Abstract
Objective To assess the efficacy and safety of pooled human albumin solutions as part of fluid volume expansion and resuscitation (with or without improvement of baseline hypoalbuminaemia) in critically unwell adults with sepsis of any severity.
Design Systematic review and meta-analysis of randomised clinical trials, with trial sequential analysis, subgroup, and meta-regression analyses.
Data sources PubMed, PubMed Central, Web of Science (includes Medline, Conference Proceedings Citation Index, Data Citation Index, Chinese Science Citation Database, CAB abstracts, Derwent Innovations Index), OvidSP (includes Embase, Ovid Medline, HMIC, PsycINFO, Maternity and Infant Care, Transport Database), Cochrane Library, clinicaltrials.gov, controlled-trials.com, online material, relevant conference proceedings, hand searching of reference lists, and contact with authors as necessary.
Eligibility criteria Prospective randomised clinical trials of adults with sepsis of any severity (with or without baseline hypoalbuminaemia) in critical or intensive care who received pooled human albumin solutions as part of fluid volume expansion and resuscitation (with or without improvement of hypoalbuminaemia) compared with those who received control fluids (crystalloid or colloid), were included if all-cause mortality outcome data were available. No restriction of language, date, publication status, or primary study endpoint was applied.
Data extraction Two reviewers independently assessed articles for inclusion, extracted data to assess risk of bias, trial methods, patients, interventions, comparisons, and outcome. The relative risk of all-cause mortality was calculated using a random effects model accounting for clinical heterogeneity.
Primary outcome measure All-cause mortality at final follow-up.
Results Eighteen articles reporting on 16 primary clinical trials that included 4190 adults in critical or intensive care with sepsis, severe sepsis, or septic shock. A median of 70.0 g daily of pooled human albumin was received over a median of 3 days by adults with a median age of 60.8 years as part of fluid volume expansion and resuscitation, with or without correction of hypoalbuminaemia. The relative risk of death was similar between albumin groups (that received a median of 175 g in total) and control fluid groups (relative risk 0.94; 95% confidence interval 0.87 to 1.01; P=0.11; I2=0%). Trial sequential analysis corrected the 95% confidence interval for random error (0.85 to 1.02; D2=0%). Eighty eight per cent of the required information size (meta-analysis sample size) of 4894 patients was achieved, and the cumulative effect size measure (z score) entered the futility area, supporting the notion of no relative benefit of albumin (GRADE quality of evidence was moderate). Evidence of no difference was also found when albumin was compared with crystalloid fluid (relative risk 0.93; 0.86 to 1.01; P=0.07; I2=0%) in 3878 patents (GRADE quality of evidence was high; 79.9% of required information size) or colloid fluids in 299 patients (relative risk 1.04; 0.79 to 1.38; P=0.76; I2=0%) (GRADE quality of evidence was very low; 5.8% of required information size). When studies at high risk of bias were excluded in a predefined subgroup analysis, the finding of no mortality benefit remained, and the cumulative z score was just outside the boundary of futility. Overall, the meta-analysis was robust to sensitivity, subgroup, meta-regression, and trial sequential analyses.
Conclusions In this analysis, human albumin solutions as part of fluid volume expansion and resuscitation for critically unwell adults with sepsis of any severity (with or without baseline hypoalbuminaemia) were not robustly effective at reducing all-cause mortality. Albumin seems to be safe in this setting, as a signal towards harm was not detected, but this analysis does not support a recommendation for use.
Introduction
The use of colloid fluids is controversial and neither the efficacy nor safety of pooled human albumin solutions has been adequately demonstrated in randomised trials or meta-analyses.1 2 3 4 Uncertainty has resulted in continued global5 albumin use and associated expense.6 Human albumin is a natural colloid used as part of volume expansion and resuscitation and to correct hypoalbuminaemia.7 8 Sepsis, severe sepsis, and septic shock have a high mortality in adults of 24-39% in hospital9 or at 28 days and 33-50% at 90 days.10 11 Fluid volume expansion and resuscitation of these critically ill patients with albumin is recommended by both the UK National Institute for Health and Care Excellence (NICE)12 and the Surviving Sepsis Campaign (GRADE 2C), based on limited evidence that is of low quality.13 14 15 The SAFE study7 reported no difference in mortality between human albumin and crystalloid (P=0.09) in 1218 randomised adults with severe sepsis, of whom 36% had septic shock.8 However, mortality reduction was reported when a subgroup (76%) with available data on covariates was subjected to multivariate logistic regression analysis (P=0.03), supported by persistent Kaplan-Meier survival curve separation observed after approximately eight days.8 Furthermore, the use of albumin to correct or improve hypoalbuminaemia is controversial. Cohort studies associate hypoalbuminaemia with increased morbidity and mortality in both heterogeneous16 and septic17 patients in critical or intensive care. COASST18 also suggested that human albumin infusion for severe sepsis was cost effective. However, randomised clinical trials report human albumin infusion improves only organ function19 and hypoalbuminaemia8 20 in these septic adults.21 Thus, it is unclear if mortality is dependent on baseline albumin concentration.
For 62% of cases human albumin infusion is not supported by consensus guideline recommendations.6 Implementation of albumin guidelines is limited by the lack of generalisability of meta-analysis findings, hindered by small information size and pooling of studies of clinically heterogeneous patient groups. A meta-analysis of 1977 patients with sepsis reported reduced mortality associated with human albumin solutions (odds ratio 0.82; 95% confidence interval 0.67 to 1.00; P=0.05).22 However, this borderline difference23 was not robust to sensitivity or subgroup analyses: there was clear evidence of subgroup difference (P=0.01) between adults with sepsis, who did not benefit with albumin (odds ratio 0.87; 0.71 to 1.07; P=0.18), and children with malaria, who did benefit (odds ratio 0.29; 0.12 to 0.72; P=0.008).22. Comparison of human albumin with unavailable or seldom used fluids is also a limitation of meta-analyses used in guidelines. Hydroxyethyl starch solutions are currently not recommended12 13 14 in critically ill adults with sepsis according to the US Food and Drug Administration (FDA)24 and European Medicines Agency (EMA)25 because of their association with increased mortality and renal morbidity.26 27 28 29 30 31 A subsequent meta-analysis that excluded the trials of hydroxyethyl starch authored by J Boldt (implicated in research misconduct),32 33 34 reported that 1435 septic adults did not benefit from human albumin (relative risk of mortality 0.90; 95% confidence interval 0.79 to 1.02; P=0.11).35
In contrast, 28 day and hospital mortality data from the EARSS and ALBIOS 2012 studies respectively (interim analysis “grey literature” included in a recent Bayesian network meta-analysis of septic adults and children with malaria) ranked albumin superior to crystalloid or hydroxyethyl starch solutions in indirect analyses designed to determine likely survival benefit.36 Hence, with emerging data from EARSS37 and ALBIOS 201438 studies on 90 day outcomes for 2602 adults with severe sepsis and septic shock, our objective was to conduct a systematic review and meta-analysis to assess the safety and efficacy of human albumin with the research question: “what is the relative effect on all-cause mortality at final follow-up39 of pooled human albumin as part of fluid volume expansion and resuscitation (with or without improvement of hypoalbuminaemia) in critical or intensive care adults with sepsis40 of any severity (with or without baseline hypoalbuminaemia) compared with control (crystalloid or colloid) fluid?” We challenged the robustness of our findings by considering study risk of bias, trial sequential analysis, and assessed moderators with predefined subgroup and meta-regression analyses.
Materials and methods
We used the Cochrane Collaboration41 methodology to undertake, and the PRISMA (Preferred Reporting Items for Systematic Reviews and Meta-Analyses)42 statement methodology to report, a systematic review and meta-analysis of randomised clinical trials. The relative effect of pooled human albumin solutions as part of fluid volume expansion and resuscitation, with or without improvement of hypoalbuminaemia, of adults in critical or intensive care with sepsis of any severity, with or without baseline hypoalbuminaemia, was investigated in comparison with control crystalloid or colloid fluid. The primary outcome measure was all-cause mortality at final follow-up,39 with predefined subgroup analyses of studies at high risk of bias compared with low or unclear risk of bias.41 43 The study was not registered.
Eligibility criteria
All of the following criteria were met for inclusion of a study:
1. Prospective randomised clinical trial reporting on adults in a critical or intensive care unit setting that have not been retracted
2. Trial or subgroup of patients diagnosed before or at randomisation with sepsis of any severity (including sepsis, severe sepsis, and septic shock), with or without baseline hypoalbuminaemia, receiving intravenous fluid as part of volume expansion and resuscitation, with or without improvement of hypoalbuminaemia
3. At least one exposure group that received intravenous human albumin solution of any concentration or type in any carrier solution after randomisation
4. At least one control group that received any intravenous fluid (crystalloid or colloid) of any strength or type in any carrier solution after randomisation
5. Availability of all-cause mortality outcome data in the patients and comparison groups identified with criteria 1 to 4.
Identification of studies
A literature search of PubMed, PubMed Central, Web of Science (includes Medline, Conference Proceedings Citation Index, Data Citation Index, Chinese Science Citation Database, CAB abstracts, Derwent Innovations Index), OvidSP (includes Embase, Ovid Medline, HMIC, PsycINFO, Maternity and Infant Care, Transport Database), and the Cochrane Library was undertaken to identify randomised clinical trials. Further unpublished studies and grey literature44 were sought from clinicaltrials.gov, controlled-trials.com, free Google search, supplementary material published online including international manufacturer and product datasheets, and relevant conference proceedings for the previous four years. The searches were last updated on 17 March 2014. The search terms used were “sepsis” with “albumin” or “albumins,” and “randomized” or “randomised.” No language, date, publication status, or predefined outcome restriction were applied. Reference lists of evaluable studies, systematic reviews, meta-analyses, narrative reviews, and reports were also hand searched for additional studies eligible for inclusion. Reference management for published studies was with Endnote X6 (Build 8318).
Selection of studies
Two reviewers independently screened and excluded the initially identified articles from the literature search on the basis of title and abstract if they were obviously not relevant. Full text articles of potentially eligible studies were independently assessed by two reviewers against the eligibility criteria. Disagreements were resolved in meetings or referred to a third reviewer for resolution.
Data extraction
For each study, data extraction was undertaken independently by two reviewers using a pre-made extraction form. Data on the following study characteristics were collected if available: centres, countries,45 dates of patient study, number of randomised patients with sepsis of any severity, trial primary reported endpoint, and time of final mortality assessment.39 To assist comparison between studies, patients were reclassified into “sepsis,” “severe sepsis,” and “septic shock” clinical severity diagnostic groups.40 Sufficient data to calculate baseline (comparison group) all-cause mortality, observed power,46 relative and absolute risk reductions, were also collected.
Baseline patient characteristics of the albumin intervention group were collected on sex, age, illness severity (SOFA,47 APACHE II,48 SAPS II49), vasopressor use and lactate level (markers of septic shock),39 albumin level, pulmonary infection focus, mechanical ventilation, acute respiratory distress syndrome, renal replacement therapy, and medical/surgical case mix. Acute respiratory distress syndrome was reclassified according to the Berlin definition50 where possible to facilitate comparison between trials.
Intervention details were extracted. The indication, intervention method, timing of intervention initiation, desired intervention targets, intervention exposure time, types of interventions (concentration of human albumin with brand and manufacturer; comparison fluid type), intervention dose (to calculate daily and total dose, total and volume), were also recorded. If more than one suitable randomised comparison group was reported, these were combined as appropriate into comparison fluid categories: control (all non-human albumin groups), crystalloid, or colloid.
Data on the predefined primary outcome of all-cause mortality were collected in relation to the patients enrolled at baseline.41 When mortality was reported at different follow-up intervals, data from the longest complete follow-up was used.39 For published studies, we contacted the corresponding author for clarification of specific sepsis mortality data for individual intervention group if required, if this had not been attempted by a previous systematic review. We also contacted the lead investigators of unpublished registered trials that had not presented data of their final mortality outcome. Data on early (≤24 hour) and post-intervention albumin levels in the pooled human albumin groups were collected, and their difference from pre-intervention baseline calculated. If these data were not reported in the text of articles, we estimated values from their figures if available.
Assessment of risk of bias
Two reviewers independently assessed the risk of bias of individual studies, and with bias domains across studies, using the Cochrane collaboration tool.41 43 RevMan version 5.2.9 (Java 6) was used to construct summaries. The domains of assessment for the outcome of all-cause mortality were selection (sequence generation and allocation concealment), performance, detection, attrition, selective reporting, research misconduct or duplicate publication, and other bias. Blinding (for performance bias assessment) of intervention fluid was considered to confer low risk of bias if healthcare staff and patients were blind to group allocation and efforts had been made to conceal fluids and administration equipment. The risk of performance bias was considered unclear if a fixed albumin dose schedule was used without blinding, or if blinding was reported but to a lesser degree than required for low risk of bias. Otherwise, if a variable albumin dose schedule was reported, the risk of bias was considered high without adequate blinding. The other bias category included a bias of any potential source.41 A trial was considered as high risk of bias overall if one or more individual bias assessment domains were judged to be at high risk. If all individual bias domains were judged to be low risk, a study was considered low risk of bias overall. If one or more individual bias assessment domains was judged to be of unclear risk of bias, the overall trial risk of bias was considered low (if reviewers judged that key domains were at low risk and the unclear risk domains were unlikely to seriously alter the results) or unclear (if key domains were judged to be at unclear risk of bias, raising some doubt about the results).41 43 Publication bias was assessed by visual judgement of a funnel plot and by Egger’s regression.51 52
Grading the quality of evidence
The quality of evidence was assessed with GRADE (Grading of Recommendations, Assessment, Development and Evaluation) methodology by a panel of four reviewers with experience of critical/intensive care medicine, haematology, anaesthesia, and general (internal) medicine.15 Quality of evidence was classified as high, moderate, low, or very low based on the judgements for the outcome of all-cause mortality regarding risk of bias, inconsistency, indirectness, imprecision, and other considerations (publication bias).15 53 GRADE was applied to each human albumin fluid comparison, then to each predefined risk of bias subgroup. Summary tables were constructed with GRADEpro version 3.6.
Statistical analysis
The primary outcome summary effect measure was relative risk of all-cause mortality39 of pooled human albumin solutions compared to control, crystalloid, or colloid fluid. Predefined subgroup analysis was by risk of bias (high compared with low or unclear risk of bias).41 Other predefined subgroup and meta-regression54 analyses were undertaken to investigate statistical, methodological, and clinical heterogeneity that may relate to effect size for each albumin comparison. Subgroups of individual bias domains were assessed (selection, performance, detection, attrition, reporting, research misconduct or duplicate publication, and other bias).41 43 Further predefined bias type subgroups were author bias (J Boldt or others),22 31 32 time bias (before or after Surviving Sepsis Campaign),13 14 31 data source bias (journal articles or conference proceedings),31 small study bias (multicentre or single centre; <100 patients per group),31 55 56 and location bias (continent).31 45 Predefined clinical subgroups were disease severity (sepsis, severe sepsis, severe sepsis and septic shock, or septic shock),40 57 58 time of all-cause mortality observation (≥90 days, ≥28 to <90 days, hospital, or intensive care unit mortality),26 39 59 intervention method (fixed or variable albumin dosing protocol)2 22 60 and type (hypooncotic (4-5%) or hyperoncotic (20%) human albumin concentration),2 22 60 intervention timing (early infusion),37 38 61 and comparison colloid type (gelatin; 6% tetrastarch 130 kDa or other hydroxyethyl starches).26 29 31 59 62 63 Predefined continuous clinical covariates were baseline sepsis or disease severity (vasopressor use and lactate as indicators of septic shock),39 40 57 58 64 baseline (comparison group) mortality, intervention duration (days of infusion), intervention exposure/dose/volume (daily and total human albumin), baseline albumin level, early (≤24 hours) and post-intervention albumin level (and respective changes from baseline).19 54 65 66 Baseline markers of sepsis related clinical covariates (pulmonary site of infection, invasive ventilation, acute respiratory distress syndrome, renal replacement therapy) were also regressed.39 As >6-10 data points are generally required to draw meaningful conclusions from meta-regression, we did not present the analysis by risk of bias if the number of studies after exclusion of those at high risk of bias was below this threshold.54
The relative risk of death for human albumin compared to control or crystalloid or colloid fluids was calculated for each included study. A pooled summary relative risk of these studies and their 95% confidence intervals was then calculated for each fluid comparison. P values of ≤0.05 and relative risk point estimate 95% confidence intervals that excluded the null (<1.00 or >1.00) were considered statistically significant. Continuity correction was not required as no zero event trials were identified. Statistical heterogeneity was assessed using the χ2 test (Cochran Q) and I2 statistic.67 68 Heterogeneity was suggested if Q>df (degrees of freedom) and present if P≤0.10. I2 values of 0-24.9%, 25-49.9%, 50-74.9%, and 75-100% were considered as none, low, moderate, and high thresholds for statistical heterogeneity.67 68 A random effects model69 (Mantel-Haenszel method) was used in the presence of statistical heterogeneity or a judgment of potential clinical heterogeneity. τ2>1 suggested heterogeneity.41 Mixed effects univariate meta-regression (unrestricted maximum likelihood) was used to allow for residual heterogeneity and to explore the observational effect of continuous covariates on effect size.41 52 54
Sensitivity analysis was performed by using a fixed effects model (Mantel-Haenszel method), odds ratios with both random and fixed effects models, exclusion of the largest trial, exclusion of the most weighted trial, and exclusion of the trial with highest observed power. Analysis by excluding studies at high risk of bias was part of a predefined subgroup analysis.41 Sensitivity analysis with trial sequential analysis was performed to correct for random error and repetitive testing of accumulating and sparse data; meta-analysis monitoring boundaries and required information size (meta-analysis sample size) were quantified, along with D2 (diversity adjusted information size) and adjusted 95% confidence intervals.70 71 72 73 Risk of type 1 error was maintained at 5% with a power of 80%. Baseline (comparison group) mortality was based on that of the included trials not at high risk of bias,59 and a clinically meaningful anticipated relative mortality reduction of 10% was used based on the lowest and most conservative value from power calculations presented for included recent sepsis trials investigating a primary mortality endpoint.37 38 Trial sequential analysis 95% confidence interval boundaries that excluded the null (<1.00 or >1.00) were considered statistically significant. The same trial sequential analysis specifications were used to model the potential effect of uncompleted registered studies. Exploratory analysis with other large trials that did not meet the inclusion criteria was also undertaken if clinical interest was considered likely.
RevMan version 5.2.9 (Java 6) was used for meta-analysis and funnel plots. TSA viewer version 0.9 β was used for trial sequential analysis. Comprehensive Meta-analysis version 2.2.064 was used for Egger’s regression and meta-regression. OpenEpi version 2.3 was used for observed power (at 95% confidence interval without continuity correction as no zero event studies were identified). Online calculators (graphpad.com and clinicalevidence.bmj.com) were used for relative and absolute risk reductions and increases, and number need to treat or harm. Microsoft Excel version 14.2.4 was used for data management and simple calculations, including means, medians, and standard deviations.
Results
The literature search is summarised in figure 1. Eighteen articles7 8 37 38 74 75 76 77 78 79 80 81 82 83 84 85 86 87 reporting 16 randomised clinical trials studied 4190 adults with sepsis, severe sepsis, and septic shock, randomised to receive pooled human albumin or comparison fluid as part of volume expansion and resuscitation (with or without improvement of baseline hypoalbuminaemia) in an intensive or critical care setting between 1982 and 2012.
Fig 1 PRISMA (Preferred Reporting Items for Systematic reviews and Meta-Analyses) flow diagram detailing the search, identification, screening, and inclusion of randomised clinical trials assessed for inclusion. Reasons for exclusions were not mutually exclusive
All trials were published in English and two were companion articles.8 85 The 90 day mortality outcome results of EARRS37 were presented orally at the 24th Annual Congress of the European Society of Intensive Care Medicine; those of ALBIOS38 were communicated to us by the senior author before publication, representing a combined total 2602 patients. Sepsis subgroup or comparison fluid group mortality data for three studies79 82 87 had been obtained from a previous author data request.2 22 Our other data requests were unsuccessful.87 Further relevant data were obtained from online sources (www.esicm.org/flash-conferences/berlin-2011) and article supplementary appendices.
Although not mutually exclusive, the exclusion of studies was because eligibility criteria were not met,19 61 88 89 90 91 92 93 94 95 96 97 98 99 100 101 102 103 duplicate publication,104 105 106, or ongoing patient recruitment without availability of mortality outcome data.107 The multicentre open-label CRISTAL61 trial reported 90 day mortality outcomes in a predefined subgroup of septic adults randomised to variable doses of colloid or crystalloid fluids, and 616 patients received albumin, which was permitted by both fluid groups for hypoalbuminaemia of <20 g/L in a non-randomised manner, and thus was excluded. RASP107 is an ongoing registered (NCT01337934) blinded Brazilian trial that will randomise 360 patients with severe sepsis to either hypooncotic (4%) human albumin or crystalloid (lactated Ringer solution). CRISTAL61 and RASP107 did not meet our inclusion criteria but were used in exploratory trial sequential analysis models for clinical interest and hypothesis generation (see online data supplement). Overall, this systematic review and meta-analysis comprises 62.1% new severe sepsis and septic shock patient information by inclusion of previously unpooled ALBIOS38 and EARSS37 90 day mortality outcome data.
Randomised trial characteristics
The study characteristics extracted from the 16 primary trials are outlined in tables 1 and 2. Three primary trials7 8 37 38 were multicentre and designed to investigate the endpoint of all-cause mortality in 3820 randomised patients with severe sepsis and septic shock. In all, 2893 patients in critical or intensive care units were randomised across Europe,37 38 74 75 76 77 78 79 82 85 86 87 1218 across Australasia,7 8 and 79 across North America.80 81 83 84 Eleven trials7 8 37 38 78 80 81 82 83 84 85 86 87 recruited 4032 patients with severe sepsis and septic shock; only three trials37 80 83 recruited 827 patients exclusively with septic shock. The median study sample size was 29 patients (range 17 to 1810). Median baseline (control fluid group) mortality was 38.0% (range 13.3% to 91.7%), and median observed study power for this outcome was only 6.0% (range 1.1% to 40.0%).
Table 1.
Characteristics of 16 randomised critical care studies reported in 18 articles included in meta-analysis, and baseline patient characteristics of the albumin intervention group (or study population). Further study information available in data supplement
| Study | Study characteristics | Diagnosis | No of patients (% male) | Baseline characteristics of patients in albumin intervention group | |||
|---|---|---|---|---|---|---|---|
| Age (years) | Serum lactate level (mmol/L) | Vasopressor use (%) | Serum albumin level (g/L) | ||||
| ALBIOS 201438 | 100 centres; Italy; Aug 2008 to Feb 2012 | Severe sepsis; septic shock | 1810 (60.1) | Median 70.0 (IQR 57-77) | Median 2.3 (IQR 1.4-4.2) | 62.6 | Mean 24.1 (6.3) |
| Boldt et al 199575 | 1 centre; Germany | Sepsis* | 30 | Median 59.3 (range 40-74) | — | — | — |
| Boldt, Heesen, et al 199674 | 1 centre; Germany | Sepsis* | 30 | Mean 54.8 (SD 10.8) | Mean 1.7 (SD 0.4) | 21.4 | — |
| Boldt, Müller, et al 199676 | 1 centre; Germany | Sepsis* | 28 (64.3) | Mean 57.5 (SD 12.3) | — | 85.7 | — |
| Boldt, Muller, et al 199677 | 1 centre; Germany | Sepsis* | 28 | Mean 61.0 (SD 10.1) | — | 53.3 | — |
| Dolecek et al 200978 | 1 centre; Czech Republic; May 2005 to Feb 2008 | Severe sepsis† | 56 (86.7) | Median 47.0 (range 19 to 81) | — | 60.0 | Mean 23.8 (SD 5.9) |
| EARSS 201137 | 29 centres; France; Jul 2006 to Mar 2010 | Septic shock | 792 (65.7) | Median 66.0 (IQR 55-76) | Median 0.2 (IQR 0.2-0.4) | 100 | Median 17.8 (IQR 14-12) |
| Friedman et al 200879 | 1 centre; Belgium | Sepsis | 42 (38.4) | Mean 66.0 (SD 14) | — | 84.6 | — |
| Haupt et al 198280 | 1 centre; USA | Septic shock | 17 (71.4) | Mean 76.0 (SD 12.8) | Mean 6.6 (SD 6.0) | 100 | — |
| Metildi et al 198481 | 1 centre; USA; Jun 1978 to May 1979 | Severe sepsis‡ | 24 (66.7) | Mean 45.0 (SD 20.5) | — | — | — |
| Palumbo et al 200682 | 1 centre; Italy | Severe sepsis; septic shock | 20 (50.0) | Mean 59.6 (SD 12.6)§ | — | — | — |
| Rackow et al 198383 | 1 centre; USA; Oct 1979 to Jun 1980 | Septic shock | 18 (71.4) | Mean 76.0 (SD 12.8) | Mean 6.0 (SD 1.8)§ | 100 | — |
| Rackow et al 198984 | 1 centre; USA | Severe sepsis | 20 (80.0) | Mean 65.1 (SD 13) | Mean 5.6 (SD 1.4) | — | — |
| SAFE 20047, 20118 | 16 centres; Australasia; Nov 2001 to Jun 2003 | Severe sepsis; septic shock | 1218 (59.6) | Mean 60.5 (SD 17.2) | — | 34.8 | Mean 25.0 (SD 7.2) |
| Van der Heijden et al 200986, Trof et al 201085 | 1 centre; Netherlands | Severe sepsis | 24 (66.7) | Mean 60.0 (SD 9) | Mean 2.0 (SD 0.9) | 67.0§ | Mean 11 (SD 2) |
| Veneman et al 200487 | 1 centre; Netherlands | Severe sepsis | 33 (27)¶; 53.3§ | Mean 72.0§ | Mean 1.3 (SD 40.2)§ | 50.0§ | Mean 15 (SD 1)§ |
IQR=interquartile range; SD=standard deviation; — =value unclear or not reported.
*Patients with septic shock excluded.
†Extravascular lung water >7 mL/kg.
‡Moderate to severe acute respiratory distress syndrome.
§Data from study population.
¶Sepsis group patients originally reported87 at odds with data supplied by the authors.22
Table 2.
Details of interventions used and outcomes measured in the 16 randomised critical care studies (reported in 18 articles) included in meta-analysis. Further study information available in online data supplement
| Study | Characteristics of fluid treatment interventions | Outcomes | |||||||
|---|---|---|---|---|---|---|---|---|---|
| Albumin (%) | Control fluid(s) | Intervention period (days) | Daily albumin dose (g) | Mean (SD) serum albumin level ≤24 hours after intervention (g/L) | Final mortality observation (days) | % baseline mortality, v (a) control, (b) crystalloid, (c) HES, (d) gelatin | % observed power v (a) control, (b) crystalloid, (c) HES, (d) gelatin | ||
| ALBIOS 201438 | 20; predefined dose | Crystalloid | 9* | 24.2 | 28.6 (5.4) | 90 | (a) 42.9 | (a) 18.5 | |
| Boldt et al 199575 | 20; variable dose | Colloid (HES†) | 5 | 70 | — | ICU | (a) 66.7 | (a) 1.1 | |
| Boldt, Heesen, et al 199674 | 20‡; variable dose | Colloid (HES†) | 5 | 84.4 | — | ICU | (a) 26.7 | (a) 5.5 | |
| Boldt, Müller, et al 199676 | 20; variable dose | Colloid (HES†) | 5 | 71.6 | — | ICU | (a) 35.7 | (a) 5.6 | |
| Boldt, Muller, et al 199677 | 20; variable dose | Colloid (HES†) | 5 | 101 | — | ICU | (a) 21.4 | (a) 22.2 | |
| Dolecek et al 200978 | 20§; predefined dose | Colloid (HES¶) | 3 | 40 | — | 28 | (a) 13.3 | (a) 15.4 | |
| EARSS 201137 | 20**; predefined dose | Crystalloid (0.9% saline) | 3 | 60 | ~24 | 90 | (a) 35.1 | (a) 2.3 | |
| Friedman et al 200879 | 4††; predefined dose | Colloid (HES‡‡) | 0.03 | 16 | — | Hospital | (a) 37 | (a) 3.9 | |
| Haupt et al 198280 | 5§§; variable dose | Crystalloid (0.9% saline§§); colloid (HES¶¶) | 1 | 155*** | — | Hospital | (a) 61.5, (b) 75.0, (c) 50.0 | (a) 5.9, (b) 2.4, (c) 11.5 | |
| Metildi et al 198481 | 5; variable dose | Crystalloid (Ringer’s lactate) | 2 | 85*** | — | Hospital | (a) 91.7 | (a) 8.7 | |
| Palumbo et al 200682 | 20; variable dose | Colloid (HES¶) | —; 5 | — | — | —; 5 | (a) 30 | (a) 6.4 | |
| Rackow et al 198383 | 5§§; variable dose | Crystalloid (0.9% saline§§); colloid (HES¶¶) | 1 | 141*** | — | Hospital | (a) 60.0, (b) 75.0, (c) 50.0 | (a) 10.3, (b) 2.4, (c) 17.9 | |
| Rackow et al 198984 | 5§§; variable dose | Colloid (HES†††) | 0.03 | 49 | — | Hospital | (a) 50 | (a) 1.1 | |
| SAFE 20047, 20118 | 4‡‡‡; variable dose | Crystalloid (0.9% saline) | 8.2 | 31.7 | ~26 | 28 | (a) 35.3 | (a) 40 | |
| Van der Heijden et al 200986, Trof et al 201085 | 5§§§; variable dose | Crystalloid (0.9% saline); colloids (HES¶¶¶; gelatin****) | 0.06 | 300 | 27 (3) | ICU | (a) 38.9, (b) 33.3, (c) 50.0, (d) 33.3 | (a) 2.3, (b) 1.1, (c) 8.0, (d) 1.1 | |
| Veneman et al 200487 | 20††††; predefined dose | Crystalloid (0.9% saline); colloid (HES‡‡‡‡) | 3 | 60 | — | 30 | (a) 56 | (a) 4.6 | |
SD=standard deviation; ICU=intensive or critical care unit; HES=hydroxyethyl starch; — =value unclear or not reported; ~ =value estimated from a graph.
* ≤28 days, median presented.
† 10% pentastarch 200 kDa.
‡ Sartorius membrane 20 kDa.
§ Immuno, Baxter.
¶ 6% tetrastarch 130 kDa (Voluven, Fresenius-Kabi).
** Vialebex, LFB.
†† Red Cross of Belgium.
‡‡ 6% or 10% pentastarch 200 kDa (HAES-steril; Fresenius).
§§ Cutter.
¶¶ 6% hetastarch (Hespan, American Critical Care).
*** Data from study population.
††† 10% pentastarch (Dupont Critical Care).
‡‡‡ Albumex, CSL.
§§§ Cealb, Sanquin.
¶¶¶ 6% pentastarch 200 kDa.
**** 4% gelatin (Gelofusin, Braun Medical, Melsungen AG).
†††† CLB.
‡‡‡‡ 10% HES (Fresenius).
Sepsis patient characteristics
Sepsis patient characteristics extracted from the 16 primary clinical trials are outlined in table 1 and the online data supplement. The median age of adults exposed to human albumin solutions was 60.8 years (range 45.0–76.0), with men representing 65.7% (range 38.4–86.7%).7 8 37 38 76 78 79 80 81 82 83 84 85 86 87 Medical patients comprised a median of 0% (range 0–78.1%) or a mean of 28.2% (standard deviation 29.2%).7 8 37 38 74 75 76 77 78 82 A disease severity summary measure was not possible because of varied scoring systems and reporting. However, the median proportion of patients who required vasopressors or inotropes (an indication of septic shock) was 64.8% (range 21.4–100%)7 8 37 38 74 76 77 78 79 80 83 85 86 87 and the median serum lactate concentration was 2.2 mmol/L (0.2–6.6 mmol/L).37 38 77 80 83 84 85 86 87 The median proportion of mechanically ventilated patients was 100% (50.0–100%),7 8 37 38 74 75 76 77 78 79 81 82 84 85 86 87 pulmonary site of infection was 44.1% (33.3–66.7%),7 8 37 38 78 81 84 85 86 and acute respiratory distress syndrome was 17.6% (0–100%).7 8 74 75 76 78 79 81 85 86 The baseline median renal replacement therapy use was 3.8% (0–22.6%) based on three studies.7 8 37 78 The median baseline serum albumin concentration was 20.8 g/L (11.0–25.0 g/L).7 8 37 38 78 85 86 87
Fluid interventions
In total, 2068 patients were exposed to pooled human albumin solutions as outlined in table 2 and the online supplement. Median albumin exposure was 175.0 g (16.0–180.0 g) for a median of 3 days (40 minutes–28 days) in a median volume of 1.7 L (0.4–3.4 L).7 8 37 38 74 75 76 77 78 79 80 81 83 84 85 86 87 Thus the median daily albumin exposure was 70.0 g (16.0–300.0 g). Early infusion7 8 within 6,37 38 12,85 86 and 24 hours74 77 87 was described in seven trials. Five studies37 38 78 79 87 used a fixed predefined protocol with a median of 40.0 g daily (range 16–60 g) for 3 days (40 minutes–28 days), representing a total median exposure of 180.0 g (16–220 g) in 0.9 L (0.4–1.1 L).
Three studies were designed to improve hypoalbuminaemia in addition to fluid volume expansion and resuscitation.37 38 87 Early (≤24 hours) improvement of hypoalbuminaemia resulted in a median albumin concentration of 26.5 g/L (24.0–28.6 g/L), representing a median increase from baseline of 5.4 g/L (1.0–16.0 g/L).7 8 37 38 85 86 The median overall post-intervention hypoalbuminaemia was 28.0 g/L (25.0–29.5 g/L), representing a median increase from baseline of 5.7 g/L (5.3–16.0 g/L) with treatment.7 8 37 38 78 85 86 ALBIOS38 and SAFE7 8 intervention protocols were ≤28 days or intensive care unit length of stay, but their respective medians were 9 and 8.2 days. The median post-intervention albumin concentration on day 7 was 27.2 g/L (25.0–29.4 g/L) for ALBIOS38 and SAFE,7 8 with a median increase from baseline of 2.8 g/L (1–4.5 g/L).
Comparison fluid exposures were crystalloids (0.9% saline, Ringer’s lactate) received in control group arms by 2122 patients,7 8 37 38 74 75 76 77 78 79 80 81 82 83 84 85 86 87 and colloids (hydroxyethyl starch, gelatin) by 156 patients.74 75 76 77 78 79 80 82 83 84 85 86 87 Exposure to 6% tetrastarch 130 kDa occurred in 36 patients across two small studies,78 82 and gelatin in six patients.85 86
Risk of bias assessment
Assessment of within study bias (internal validity) is summarised in figure 2. All studies were judged to be of unclear risk of bias in at least one bias assessment domain. Ten studies74 75 76 77 80 81 82 83 84 87 had at least one high risk of bias judgment for the outcome of mortality, and were therefore considered at high risk of bias overall. The remaining six studies7 8 37 38 78 79 85 86 were considered at low risk of bias overall as reviewers judged that key domains were at low risk of bias and the domains at unclear risk of bias were unlikely to have seriously altered the results for the outcome of all-cause mortality.
Fig 2 Risk of bias summary displaying review authors’ judgments about each risk of bias domain for each included study. Randomised clinical trials are listed alphabetically by author or study name
SAFE,7 8 ALBIOS,38 and EARSS37 were the only large high quality studies designed to assess the endpoint of mortality, and reported on 3820 patients with severe sepsis and septic shock. However, only EARSS37 and ALBIOS38 collected 90 day mortality data on 2602 patients, of whom 1927 had septic shock. ALBIOS reported baseline group imbalance for central venous oxygen saturation (P=0.02) and organ dysfunction (P=0.04).38 Full publication of EARSS is awaited.37 SAFE7 8 was the only double blind study that adequately concealed fluid group allocation in 1218 patients, and would have been classified as low risk of bias for all assessment domains had baseline blood pressure been similar between groups (P=0.03). To prevent the unnecessary introduction of bias that would have classified SAFE 2011 as at high risk of bias,35 41 108 109 28 day mortality outcome data from SAFE 20047 was used rather than multivariate adjusted data from SAFE 2011,8 which excluded 24.5% of enrolled patients. All the other studies described patients exposed to open-label fluid interventions, with a variable dosing schedule, except for five that used a predefined fixed dose.37 38 78 79 87
Bias domains were judged as high risk of bias because: variable dose fluid exposures were not associated with any attempts at blinding,80 81 82 83 84 there was inconsistency between the originally reported87 27 severe sepsis patients and the author supplied group mortality data on 33 sepsis patients,22 risk of duplicate publication bias affecting 35 patients,80 83 risk of research misconduct in studies affecting 116 patients,74 75 76 77 and pre-randomisation interventions that might enhance or diminish the effect of the randomised fluids. Overall, 10 studies74 75 76 77 80 81 82 83 84 87 at high risk of bias studied 248 patients, comprising 5.9% of the patient data in this systematic review and meta-analysis.
The assessment of bias risk domains across studies (external validity) shows that, although all bias domains, except detection bias, had unclear or high risk, overall most of the information for the outcome of all-cause mortality came from data at low risk of bias (online supplement).
Primary clinical outcome: all-cause mortality
All-cause mortality with albumin compared with control fluid
Mortality data were available for 16 randomised clinical trials including 4190 patients with sepsis, severe sepsis, and septic shock who received either human albumin solutions or control fluids. The required information size was 4894 patients for 80% power and an α of 0.05. All-cause mortality was statistically similar between these two fluid groups (relative risk 0.94; 95% confidence interval 0.87 to 1.01; P=0.11) (fig 3). Statistical heterogeneity was not present (I2=0%; χ2 5.61, df=15, P=0.99; τ2 0.00). The finding was robust to sensitivity analysis (lowest P value 0.06) (tables 3 and 4, plus online supplement), and clear evidence of publication bias was not present (P=0.29). Trial sequential analysis correction of the 95% confidence interval (0.87 to 1.02; D2=0%) did not alter the finding of no mortality benefit with human albumin (fig 4).
Fig 3 Relative risk of all-cause mortality in patients exposed to human albumin solutions compared with exposure to control fluids in the 16 randomised clinical trials included in analysis. Studies are ordered chronologically within subgroups
Table 3.
Predefined clinical subgroup analysis with relative risk effect size measure using a random effects model (Mantel-Haenszel) and precision for the comparisons of albumin with control, crystalloid, and colloid fluid (see online supplement for a more comprehensive version of this table that includes predefined sensitivity and bias subgroup analyses)
| Category | Subgroups | No of studies | No of patients | Point estimate (95%CI) | P value | Group heterogeneity | Subgroup difference | ||||
|---|---|---|---|---|---|---|---|---|---|---|---|
| I2 | χ2 P value | I2 | χ2 P value | ||||||||
| Human albumin compared with control fluid | |||||||||||
| Disease severity (sepsis v severe sepsis and/or septic shock) | Severe sepsis and/or septic shock | 11 | 3854 | 0.94 (0.87 to 1.01) | 0.09 | 0 | 0.96 | 0 | 0.55 | ||
| Sepsis | 5 | 336 | 1.15 (0.73 to 1.51) | 0.80 | 0 | 0.79 | NA | NA | |||
| Disease severity (sepsis v severe sepsis v septic shock) | All studies | 16 | 4190 | 0.94 (0.87 to 1.01) | 0.08 | 0 | 0.88 | 0 | 0.76 | ||
| Septic shock | 4 | 1962 | 0.92 (0.83 to 1.02) | 0.10 | 0 | 0.45 | NA | NA | |||
| Severe sepsis | 8 | 2070 | 0.95 (0.85 to 1.06) | 0.35 | 0 | 0.67 | NA | NA | |||
| Sepsis | 5 | 336 | 1.15 (0.73 to 1.51) | 0.80 | 0 | 0.79 | NA | NA | |||
| Intervention method | Predefined | 4 | 2691 | 0.95 (0.87 to 1.05) | 0.31 | 0 | 0.77 | 0 | 0.64 | ||
| Variable | 16 | 1499 | 0.92 (0.81 to 1.04) | 0.18 | 0 | 0.96 | NA | NA | |||
| Intervention type | Hypooncotic (4-5% albumin) | 7 | 1363 | 0.90 (0.79 to 1.03) | 0.13 | 0 | 0.92 | 0 | 0.47 | ||
| Hyperoncotic (20% albumin) | 9 | 2827 | 0.96 (0.87 to 1.05) | 0.35 | 0 | 0.92 | NA | NA | |||
| Intervention timing | Early (<24 hours) | 6 | 3907 | 0.93 (0.86 to 1.01) | 0.10 | 0 | 0.89 | 0 | 0.69 | ||
| Not described/other timing | 10 | 283 | 0.98 (0.80 to 1.20) | 0.82 | 0 | 0.93 | NA | NA | |||
| Time of mortality observation | 90 day | 2 | 2602 | 0.95 (0.87 to 1.05) | 0.32 | 0 | 0.69 | 0 | 0.72 | ||
| 28-30 day | 3 | 1307 | 0.88 (0.75 to 1.02) | 0.09 | 0 | 0.58 | NA | NA | |||
| Hospital | 5 | 122 | 0.99 (0.78 to 1.26) | 0.96 | 0 | 0.80 | NA | NA | |||
| ICU | 6 | 160 | 1.03 (0.72 to 1.48) | 0.88 | 0 | 0.86 | NA | NA | |||
| Human albumin compared to crystalloid fluid | |||||||||||
| Disease severity (sepsis v severe sepsis and/or septic shock) | Severe sepsis and/or septic shock | 7 | 3878 | 0.93 (0.86 to 1.01) | 0.07 | 0 | 0.98 | NA | NA | ||
| Sepsis | 0 | 0 | NA | NA | NA | NA | NA | NA | |||
| Disease severity (sepsis v severe sepsis v septic shock) | All studies | 7 | 3878 | 0.93 (0.86 to 1.00 | 0.05 | 0 | 0.63 | 0 | 0.56 | ||
| Septic shock | 4 | 1949 | 0.91 (0.82 to 1.01 | 0.06 | 0 | 0.77 | NA | NA | |||
| Severe sepsis | 4 | 1929 | 0.96 (0.83 to 1.10) | 0.55 | 0 | 0.29 | NA | NA | |||
| Sepsis | 0 | 0 | NA | NA | NA | NA | NA | NA | |||
| Intervention method | Predefined | 2 | 2602 | 0.95 (0.87 to 1.05) | 0.32 | 0 | 0.69 | 0 | 0.32 | ||
| Variable | 5 | 1276 | 0.88 (0.77 to 1.01) | 0.08 | 0 | 1.00 | NA | NA | |||
| Intervention type | Hypooncotic (4-5% albumin) | 5 | 1276 | 0.88 (0.77 to 1.01) | 0.08 | 0 | 1.00 | 0 | 0.33 | ||
| Hyperoncotic (20% albumin) | 2 | 2602 | 0.95 (0.87 to 1.05) | 0.32 | 0 | 0.69 | NA | NA | |||
| Intervention timing | Early (<24 hours) | 4 | 3832 | 0.93 (0.86 to 1.01) | 0.12 | 0 | 0.78 | 0 | 0.93 | ||
| Not described/other timing | 3 | 46 | 0.92 (0.71 to 1.20) | 0.53 | 0 | 0.99 | NA | NA | |||
| Time of mortality observation | 90 day | 2 | 2602 | 0.95 (0.87 to 1.05) | 0.32 | 0 | 0.69 | 0 | 0.82 | ||
| 28-30 day | 1 | 1218 | 0.87 (0.74 to 1.02) | 0.09 | NA | NA | NA | NA | |||
| Hospital | 3 | 46 | 0.92 (0.71 to 1.20) | 0.53 | 0 | 0.99 | NA | NA | |||
| ICU | 1 | 12 | 1.00 (0.20 to 4.95) | 1.00 | NA | NA | NA | NA | |||
| Human albumin compared to colloid fluid | |||||||||||
| Disease severity (sepsis v severe sepsis and/or septic shock) | Severe sepsis and/or septic shock | 7 | 141 | 1.04 (0.68 to 1.59) | 0.86 | 0 | 0.71 | 0 | 0.98 | ||
| Sepsis | 5 | 158 | 1.05 (0.73 to 1.51) | 0.80 | 0 | 0.79 | NA | NA | |||
| Disease severity (sepsis v severe sepsis v septic shock) | All studies | 11 | 299 | 1.04 (0.79 to 1.38) | 0.76 | 0 | 0.92 | 8.0 | 0.34 | ||
| Septic shock | 2 | 27 | 1.54 (0.78 to 3.01) | 0.21 | 0 | 0.82 | NA | NA | |||
| Severe sepsis | 4 | 114 | 0.80 (0.46 to 1.39) | 0.43 | 0 | 0.90 | NA | NA | |||
| Sepsis | 5 | 158 | 1.05 (0.73 to 1.51) | 0.80 | 0 | 0.79 | NA | NA | |||
| Intervention method | Predefined | 2 | 98 | 0.77 (0.38 to 1.53) | 0.45 | 0 | 0.54 | 0 | 0.34 | ||
| Variable | 9 | 201 | 1.11 (0.82 to 1.50) | 0.51 | 0 | 0.92 | NA | NA | |||
| Intervention type | Hypooncotic (4-5% albumin) | 5 | 107 | 1.13 (0.74 to 1.74) | 0.57 | 0 | 0.83 | 0 | 0.62 | ||
| Hyperoncotic (20% albumin) | 6 | 192 | 0.99 (0.69 to 1.41) | 0.94 | 0 | 0.74 | NA | NA | |||
| Intervention timing | Early (<24 hours) | 2 | 48 | 1.04 (0.45 to 2.42) | 0.93 | 0 | 0.61 | 0 | 0.99 | ||
| Not described/other timing | 9 | 251 | 1.05 (0.78 to 1.40) | 0.77 | 0 | 0.84 | NA | NA | |||
| 28-30 day | 1 | 56 | 0.58 (0.18 to 1.83) | 0.35 | NA | NA | NA | NA | |||
| Hospital | 4 | 89 | 1.18 (0.75 to 1.86) | 0.47 | 0 | 0.76 | NA | NA | |||
| ICU | 6 | 154 | 1.02 (0.71 to 1.47) | 0.90 | 0 | 0.85 | NA | NA | |||
| Colloid type: HES | 6% tetrastarch 130 kDa | 2 | 76 | 0.65 (0.28 to 1.51) | 0.32 | 0 | 0.76 | 26.3 | 0.24 | ||
| Other | 9 | 223 | 1.11 (0.83 to 1.48) | 0.50 | 0 | 0.93 | NA | NA | |||
| Colloid type: gelatin | Gelatin | 1 | 12 | 1.00 (0.20 to 4.95) | 1 | NA | NA | NA | NA | ||
NA= not applicable. ICU=intensive or critical care unit. HES= hydroxyethyl starch.
Table 4.
Mixed effect meta-regression (unrestricted maximum likelihood) slope effect size, precision, and heterogeneity for the comparisons of albumin with control, crystalloid, and colloid fluid (see online supplement for a more comprehensive version of this table that includes predefined sensitivity and bias subgroup analyses)
| Category | Covariate | No of studies | No of patients | Point estimate (95%CI) | P value | τ2 |
|---|---|---|---|---|---|---|
| Human albumin compared with control fluid | ||||||
| Baseline mortality risk | Comparison group mortality | 16 | 4190 | 0.0007 (−0.0046 to 0.0061) | 0.79 | 0 |
| Baseline septic shock | Vasopressor use | 12 | 4096 | 0.0018 (-0.0177 to 0.0544) | 0.32 | 0 |
| Baseline septic shock | Lactate | 8 | 2742 | 0.0136 (−0.0589 to 0.0860) | 0.71 | 0 |
| Baseline hypoalbuminaemia | Baseline albumin level | 6 | 3933 | −0.0124 (−0.0407 to 0.0159) | 0.39 | 0 |
| Daily intervention exposure | Daily albumin dose | 15 | 4170 | 0.0013 (−0.0013 to 0.0038) | 0.33 | 0 |
| Total intervention exposure | Total albumin dose | 15 | 4170 | 0.0006 (−0.0005 to 0.0018) | 0.26 | 0 |
| Early intervention response | Day 1 post-intervention albumin | 4 | 3844 | 0.0007 (−0.0454 to 0.0440) | 0.97 | 0 |
| Intervention response | Post-intervention albumin level | 5 | 3900 | 0.0173 (−0.0268 to 0.0613) | 0.44 | 0 |
| Intervention response | Post-intervention increase in albumin level | 5 | 3903 | 0.0116 (−0.0120 to 0.0352) | 0.34 | 0 |
| Human albumin compared to crystalloid fluid | ||||||
| Baseline mortality risk | Comparison group mortality | 7 | 3878 | 0.0000 (−0.0055 to 0.0054) | 0.98 | 0 |
| Baseline septic shock | Vasopressor use | 6 | 3854 | 0.0018 (−0.0018 to 0.0055) | 0.33 | 0 |
| Baseline septic shock | Lactate | 5 | 2636 | 0.0117 (−0.0895 to 0.0661) | 0.77 | 0 |
| Baseline hypoalbuminaemia | Baseline albumin level | 4 | 3832 | −0.0 129 (−0.0427 to 0.0189) | 0.45 | 0 |
| Daily intervention exposure | Daily albumin dose | 7 | 3878 | 0.0003 (−0.0025 to 0.0031) | 0.82 | 0 |
| Total intervention exposure | Total albumin dose | 7 | 3878 | 0.0006 (−0.0009 to 0.0022) | 0.41 | 0 |
| Early intervention response | Day 1 post-intervention albumin | 4 | 3832 | 0.0074 (−0.0454 to 0.0440) | 0.97 | 0 |
| Intervention response | Post-intervention albumin level | 4 | 3832 | 0.0182 (−0.0259 to 0.0624) | 0.42 | 0 |
| Intervention response | Post-intervention increase in albumin level | 4 | 3832 | 0.0124 (−0.0114 to 0.0362) | 0.31 | 0 |
| Human albumin compared to colloid fluid | ||||||
| Baseline mortality risk | Comparison group mortality | 11 | 299 | 0.0022 (−0.0143 to 0.0187) | 0.79 | 0 |
| Baseline septic shock | Vasopressor use | 8 | 229 | 0.0090 (−0.0162 to 0.0144) | 0.91 | 0 |
| Baseline septic shock | Lactate | 5 | 99 | 0.0025 (−0.2359 to 0.02409) | 0.98 | 0 |
| Baseline hypoalbuminaemia | Baseline albumin level | 2 | 80 | NA | NA | NA |
| Daily intervention exposure | Daily albumin dose | 10 | 279 | 0.0015 (−0.0032 to 0.0061) | 0.54 | 0 |
| Total intervention exposure | Total albumin dose | 10 | 279 | 0.0004 (−0.0001 to 0.0023) | 0.64 | 0 |
| Early intervention response | Day 1 post-intervention albumin | 1 | 24 | NA | NA | NA |
| Intervention response | Post-intervention albumin level | 2 | 80 | NA | NA | NA |
| Intervention response | Post-intervention increase in albumin level | 2 | 80 | NA | NA | NA |
NA= not applicable.
Fig 4 Trial sequential analysis of trials reporting mortality comparing pooled human albumin solutions with control fluids. Upper graph shows trial sequential analysis of the 16 primary trials; lower graph shows analysis of 6 primary trials after exclusion of studies at high risk of bias. A diversity adjusted information size of 4894 patients was calculated using α=0.05 (two sided), β=0.20 (power 80%), D2=0%, an anticipated relative risk of 10.0%, and an event proportion of 38.6% in the control arm. The cumulative z curve was constructed using a random effects model, and a penalised z curve was also constructed. For all studies, the relative risk was 0.94, and the 95% confidence interval was corrected to 0.87 to 1.02, from 0.87 to 1.01. After exclusion of studies at high risk of bias, relative risk was 0.93 and the 95% confidence interval of 0.86 to 1.01 was corrected to 0.84 to 1.02.
Predefined subgroup, meta-regression, and trial sequential analyses are summarised in tables 3 and 4 (see also the online supplement). The test for subgroup difference demonstrated a trend for the risk of bias domain “research misconduct or duplicate publication” bias (I2=38.6, χ2=1.63, df=1, P=0.20). A borderline trend towards benefit of albumin was observed after studies at high risk of bias for this bias domain were excluded (relative risk 0.93; 95% confidence interval 0.86 to 1.00; P=0.06). Baseline hypoalbuminaemia, albumin improvement, or sepsis severity (including subgroup analysis by baseline septic shock: relative risk 0.92; 0.83 to 1.02; P=0.10) determined in different ways were not robustly associated with improved survival in albumin treated patients (tables 3 and 4, online supplement).
The cumulative z score crosses the boundary of futility, suggesting further trials are not required as they are unlikely to demonstrate reduced mortality with albumin, and even less likely to show increased mortality (fig 4). A model including the ongoing RASP trial107 increased the information size to 93.0%, but this still did not alter the finding of no overall mortality benefit (online supplement). This was also the case for the model including patients with sepsis who received albumin in the CRISTAL trial61 (online supplement).
Overall, with 85.6% of the required information size, the number needed to treat was 37 patients (95% confidence interval: the number needed to treat is >18, and the number needed to harm is >517) for the comparison of albumin with control fluid. GRADE quality of evidence was judged to be moderate (table 5).
Table 5.
GRADE quality of evidence summary table for the comparisons of human albumin with control, crystalloid, or colloid fluid for adults with sepsis of any severity in critical or intensive care
| Quality assessment for comparison | No of patients | Effect | Quality | Importance | ||||||||||
|---|---|---|---|---|---|---|---|---|---|---|---|---|---|---|
| No of studies | Design | Risk of bias | Inconsistency | Indirectness | Imprecision | Other considerations | Human albumin | Compared fluid | Relative risk (95% CI) | Absolute | ||||
| Quality assessment for the comparison of human albumin with control fluid | ||||||||||||||
| All-cause mortality (follow-up ICU discharge to 90 days observation): | ||||||||||||||
| 16 | RCT | Serious* | No serious inconsistency | No serious indirectness | No serious imprecision | None | 757/2068 (36.6%) | 835/2122 (39.3%) | 0.94 (0.87 to 1.01) | 2 fewer per 100 (from 5 fewer to 0 more) | +++ Moderate | Critical | ||
| All-cause mortality in studies at low or unclear risk of bias (follow-up ICU discharge to 90 days observation): | ||||||||||||||
| 6 | RCT | No serious risk | No serious inconsistency | No serious indirectness | No serious imprecision | None | 699/1956 (35.7%) | 767/1986 (38.6%) | 0.93 (0.86 to 1.01) | 3 fewer per 100 (from 5 fewer to 0 more) | ++++ High | Critical | ||
| All-cause mortality in studies at high risk of bias (follow-up ICU discharge to 30 days observation): | ||||||||||||||
| 10 | RCT | Serious† | No serious inconsistency | Serious‡ | Serious§ | None | 58/112 (51.8%) | 68/136 (50%) | 1.02 (0.83 to 1.24) | 1 more per 100 (from 9 fewer to 12 more) | + Very low | Critical | ||
| Quality assessment for the comparison of human albumin with crystalloid fluid | ||||||||||||||
| All-cause mortality (follow-up ICU discharge to 90 days observation): | ||||||||||||||
| 7 | RCT | No serious risk | No serious inconsistency | No serious indirectness | No serious imprecision | None | 710/1937 (36.7%) | 763/1941 (39.3%) | 0.93 (0.86 to 1.01) | 3 fewer per 100 (from 6 fewer to 0 more) | ++++ High | Critical | ||
| All-cause mortality in studies at low or unclear risk of bias (follow-up ICU discharge to 90 days observation): | ||||||||||||||
| 4 | RCT | No serious risk | No serious inconsistency | No serious indirectness | No serious imprecision | None | 690/1911 (36.1%) | 746/1921 (38.8%) | 0.93 (0.86 to 1.01) | 3 fewer per 100 (from 5 fewer to 0 more) | ++++ High | Critical | ||
| All-cause mortality in studies at high risk of bias (follow-up hospital discharge observation): | ||||||||||||||
| 3 | RCT | Serious† | No serious inconsistency | No serious indirectness | Serious§ | None | 20/26 (76.9%) | 17/20 (85.0%) | 0.92 (0.71 to 1.20) | 7 fewer per 100 (from 25 fewer to 17 more) | ++ Low | Critical | ||
| Quality assessment for the comparison of human albumin with colloid fluid | ||||||||||||||
| All-cause mortality (follow-up ICU discharge to 28 days observation): | ||||||||||||||
| 11 | RCT | Serious¶ | No serious inconsistency | Serious‡ | Serious§ | None | 54/143 (37.8%) | 58/156 (37.2%) | 1.04 (0.79 to 1.38) | 1 more per 100 (from 8 fewer to 14 more) | + Very low | Critical | ||
| All-cause mortality in studies at low or unclear risk of bias (follow-up ICU discharge to 28 days observation): | ||||||||||||||
| 3 | RCT | No serious risk | No serious inconsistency | Serious‡ | Serious§ | None | 11/51 (21.6%) | 21/65 (32.3%) | 0.77 (0.42 to 1.43) | 7 fewer per 100 (from 19 fewer to 14 more) | ++ Low | Critical | ||
| All-cause mortality in studies at high risk of bias (follow-up ICU discharge to hospital discharge observation): | ||||||||||||||
| 8 | RCT | Serious† | No serious inconsistency | Serious‡ | Serious§ | None | 43/92 (46.7%) | 37/91 (40.7%) | 1.13 (0.83 to 1.53) | 5 more per 100 (from 7 fewer to 22 more) | + Very low | Critical | ||
ICU=intensive or critical care unit. RCT=randomised clinical trial.
*5.9% of patients were in studies judged as high risk of bias.
†All studies judged as high risk of bias.
‡Most patients were compared with high molecular weight hydroxyethyl starches that are now seldom available or used for adults with sepsis in critical or intensive care. This class of synthetic colloid has been associated with harm, and the European Medicines Agency on 6 March 2014 and the Food and Drug Administration on 25 November 2013 have concluded that hydroxyethyl starches solutions are no longer permitted for use in critically unwell adults with sepsis in parts of Europe and the US.24 25
§Wide 95% confidence intervals, most included studies are small, and the information size is low.
¶61.2% patients were in studies judged as high risk of bias.
All-cause mortality with albumin compared with control fluid by risk of bias
Exclusion of trials at high risk of bias left six studies including 3942 patients, which moved the point estimate further towards benefit with human albumin (relative risk 0.93; 95% confidence interval 0.86 to 1.01; P=0.07), but this was not statistically significant (fig 3). The required information size was 4894. Statistical heterogeneity was not present (I2=0%; χ2 1.76, df=5, P=0.88; τ2 0.00). Overall, the finding was robust to sensitivity analysis, although a trend towards borderline statistical significance (lowest P value 0.06) was observed, particularly with a fixed effects model (relative risk 0.93; 0.85 to 1.00; P=0.06) (online supplement). Clear evidence of publication bias was not present (P=0.39). Trial sequential analysis correction of the 95% confidence interval (0.85 to 1.02; D2=0%) did not alter the notion of no benefit with albumin.
In the trial sequential analysis, the cumulative z score is close to the boundary of futility and further from the sequential monitoring boundary of benefit (fig 4), indicating that further studies are unlikely to alter the conclusion of no benefit with albumin. A model including data from RASP107 increased the information size to 87.9% when attributed a relative risk of 0.9, resulting in the cumulative z score touching the conventional boundary of benefit (P=0.05) but not the trial sequential monitoring boundary of benefit (corrected 95% confidence interval 0.85 to 1.02; D2=0%) (online supplement). However, an exploratory model including patients with sepsis from the CRISTAL trial61 who received only albumin was not associated with survival benefit, although this study would probably be considered high risk of bias and thus excluded from this analysis, and is mentioned here for clinical interest only (online supplement).
Overall, the tests for subgroup difference and heterogeneity were not statistically significant between studies at high risk of bias (that included 248 patients) and studies at low or unclear risk of bias (fig 3). However, statistical heterogeneity that was low was introduced (I2=27.1%, χ2=1.37, df=1, P=0.24) with a fixed effects model using relative risk estimates (tables 3 and 4, online supplement). When studies at low risk of bias were examined by sepsis subgroup (sepsis, severe sepsis, septic shock), no statistically significant benefit was observed for each individual group (for septic shock, relative risk 0.91; 95% confidence interval 0.81 to 1.01; P=0.09), but overall borderline benefit was demonstrated (relative risk 0.92; 0.85 to 1.00; P=0.05) (online supplement). However, this was not robust to trial sequential analysis correction of the 95% confidence interval (0.84 to 1.01; D2=0%) (online supplement), and sensitivity analysis as the null could not be excluded: fixed effects model (relative risk 0.93;0.85 to 1.00; P=0.06); odds ratios with a random effects model (odds ratio 0.89; 0.77 to 1.00; P=0.08) or fixed effects model (odds ratio 0.88; 0.78 to 1.01; P=0.06). Furthermore, the finding was not robust to exclusion of either SAFE7 8 or ALBIOS.38 No benefit with albumin was also observed when severe sepsis and septic shock were grouped together (tables 3 and 4, online supplement).
Overall, with 80.5% of the required information size, the number needed to treat was 37 patients (95% confidence interval: number needed to treat is >18 and the number needed to harm is >297) for the comparison of albumin with control fluid excluding trials at high risk of bias. The overall GRADE quality of evidence was judged to be high (table 5).
All-cause mortality with albumin compared with crystalloid fluids
Seven clinical trials randomised 3878 patients and compared human albumin with crystalloid fluids. The required information size was 4856 patients for 80% power and an α of 0.05. Mortality was similar for both fluid groups (relative risk 0.93; 95% confidence interval 0.86 to 1.01; P=0.07) (fig 5). Statistical heterogeneity was not present (I2=0%; χ2=1.12, df=6, P=0.98; τ2=0.00). The finding was robust to sensitivity analyses (tables 3 and 4, online supplement). Clear evidence of publication bias was not detected (P=0.91). Trial sequential analysis correction of the 95% confidence interval (0.85 to 1.02; D2=0%) did not alter the finding of no mortality benefit with human albumin (fig 6).
Fig 5 Relative risk of all-cause mortality in patients exposed to human albumin solutions compared with exposure to crystalloid fluids in seven clinical trials. Studies are ordered chronologically within subgroups
Fig 6 Trial sequential analysis of trials reporting mortality comparing pooled human albumin solutions with crystalloid fluids. Upper graph shows trial sequential analysis of the seven primary trials; lower graph shows analysis of four primary trials after exclusion of studies at high risk of bias. A diversity adjusted information size of 4856 patients was calculated using α=0.05 (two sided), β=0.20 (power 80%), D2=0%, an anticipated relative risk of 10.0%, and an event proportion of 38.8% in the control arm. The cumulative z curve was constructed using a random effects model, and a penalised z curve was also constructed. For all studies, the relative risk was 0.93, and the 95% confidence interval was corrected to 0.85 to 1.02, from 0.86 to 1.01. After exclusion of studies at high risk of bias, relative risk was 0.93 and the 95% confidence interval of 0.86 to 1.01 was corrected to 0.85 to 1.02.
Predefined subgroup and meta-regression analyses are summarised in tables 3 and 4 (plus online supplement); these did not alter the finding of no benefit with albumin, except when sepsis severity subgroups were used by separating ALBIOS38 severe sepsis and septic shock patient data (these were post hoc unadjusted outcomes). There was statistically significant overall benefit observed with albumin (relative risk 0.93; 95% confidence interval 0.86 to 1.00; P=0.05), but no single sepsis severity subgroup benefited. The strongest borderline trend was observed in the septic shock subgroup (relative risk 0.91; 0.82 to 1.01; P=0.06). However, the overall signal of benefit was not robust to sensitivity analyses: fixed effects model (relative risk 0.93; 0.86 to 1.01; P=0.07; I2=0%); odds ratios with random or fixed effects models (odds ratio 0.89; 0.78 to 1.01; P=0.07; I2=0%); exclusion of SAFE7 8 (relative risk 0.94; 0.86 to 1.03; P=0.19; I2=51.3%) or ALBIOS38 (relative risk 0.92; 0.82 to 1.02; P=0.13; I2=0%). Trial sequential analysis correction of the 95% confidence interval (0.85 to 1.01; D2=0%), and the observation that the cumulative z score did not reach the trial sequential monitoring boundary of benefit (online supplement) support the view that albumin was not beneficial or harmful. Furthermore, survival benefit was not observed when other markers of septic shock were used for meta-regression analysis (table 4), and the septic shock subgroup itself was not robust to sensitivity or trial sequential analyses (online supplement).
The cumulative z score is between the conventional α boundary of 0.05 and the futility boundary, but further from the corrected significance trial sequential monitoring boundary for benefit (fig 6). In a model where the ongoing RASP study107 was assigned a relative risk of 0.9, the information size increased to 87.3%, resulting in the cumulative z score touching the conventional α boundary of benefit (P=0.05) but not the trial sequential monitoring boundary of benefit (95% confidence interval 0.85 to 1.01; D2=0%) (online supplement). Exploratory modelling using patients who received only albumin infusion in both treatment arms of CRISTAL61 did not alter the conclusion of no mortality benefit as the cumulative z score crossed the futility boundary (online supplement).
Overall, with 79.9% of the required information size, the number needed to treat was 38 patients (95% confidence interval: the number needed to treat is >18, and the number needed to harm is >251) for the comparison of albumin with crystalloid fluid. The overall GRADE quality of evidence was judged to be high (table 5).
All-cause mortality with albumin compared with crystalloid fluids by risk of bias
Figure 5 shows the analysis of predefined subgroups based on risk of bias. With exclusion of four trials at high risk studying 46 patients, 3832 patients in four trials remain (fig 6). The information size was 4856. The finding of no difference between groups persists (relative risk 0.93; 95% confidence interval 0.86 to 1.01; P=0.08), without evidence of subgroup heterogeneity (I2=0%; χ2=1.09, df=3, P=0.78; τ2=0.00). These findings were robust to sensitivity analysis (online supplement). Clear evidence of publication bias was not evident (P=0.94). Trial sequential analysis reduced precision (0.85 to 1.02; D2=0%).
The cumulative z score moves closer to the futility boundary when trials at high risk of bias are excluded (fig 6). A model including RASP107 increased the information size to 91.6%, but this does not alter the conclusion of no mortality benefit with albumin (online supplement). An exploratory model with CRISTAL61 including septic patients who received albumin also did not alter this conclusion, and is included only for interest, as this study is unlikely to be retained in this group after exclusion of studies at high risk of bias (online supplement).
There was no benefit with albumin observed by sepsis severity subgroups (relative risk 0.93; 0.85 to 1.03; P=0.18) after exclusion of studies at high risk of bias (online supplement). The greatest trend towards possible benefit remained in the septic shock subgroup (relative risk 0.91; 0.81 to 1.01; P=0.09). These findings were not altered by sensitivity analysis; albumin did not improve survival for patients with sepsis when ALBIOS38 severe sepsis and septic shock patients were analysed in separate subgroups, and the finding was robust to trial sequential analysis (online supplement).
Overall, with 78.9% of the required information size, the number needed to treat was 37 patients (95% confidence interval: the number needed to treat is >18, and the number needed to harm is to >297) for the comparison of albumin with crystalloid fluid, after excluding trials at high risk of bias. The overall GRADE quality of evidence was judged to be high (table 5).
All-cause mortality with albumin compared with colloid fluids
Eleven trials that randomised 299 patients compared human albumin with colloids, which were mainly hydroxyethyl starches; 36 patients were exposed to 6% tetrastarch 130 kDa, and six to gelatin. No difference was evident for all-cause mortality (relative risk 1.04; 95% confidence interval 0.79 to 1.38; P=0.76) (fig 7) and statistical heterogeneity was not present (I2=0%; χ2=4.47, df=10, P=0.92; τ2=0.00). The finding withstood sensitivity analysis (tables 3 and 4, plus online supplement). Clear evidence of publication bias was not present (P=0.98). Trial sequential analysis was not possible because the information size was too low to display a meaningful futility boundary given the required information size was 5183.
Fig 7 Relative risk of all-cause mortality in patients exposed to human albumin solutions compared with exposure to colloid fluids in 11 trials. Studies are ordered chronologically within subgroups
Tables 3 and 4 (plus online supplement) summarise predefined subgroup and meta-regression analyses. The test for subgroup difference suggested a trend towards an effect of the risk of bias domain “research misconduct or duplicate publication bias” (I2=33.0, χ2=1.49, df=1, P=0.22), time bias stratified by the Surviving Sepsis Campaign110 111 (I2=38.1, χ2=1.62, df=1, P=0.20), hydroxyethyl starch (colloid) type (I2=26.3, χ2=1.36, df=1, P=0.24), and disease severity (sepsis, severe sepsis, septic shock) (I2=8.0, χ2=2.17, df=1, P=0.34). No survival benefit in patients with septic shock defined in different ways was observed in subgroup (relative risk 1.04; 95% confidence interval 0.79 to 1.38; P=0.76) or meta-regression analyses (table 4, online supplement).
Overall, with 5.8% of the required information size, the number needed to harm was 172 patients (95% confidence interval: the number needed to harm is >9, and the number needed to treat is >10) for the comparison of albumin with colloid fluid. The overall GRADE quality of evidence was judged to be very low (table 5).
All-cause mortality with albumin compared with colloid fluids by risk of bias
Three studies with 116 patients were not at high risk of bias for the comparison of human albumin with colloids (fig 7). No difference in mortality was detected (relative risk 0.77; 95% confidence interval 0.42 to 1.43; P=0.41) and statistical heterogeneity was not present (I2=0%; χ2=0.37, df=2, P=0.83; τ2=0.00). Sensitivity analysis did not alter this finding (tables 3 and 4, plus online supplement). Clear evidence of publication bias was lacking (P=0.61). Trial sequential analysis was not possible as the information size was too low.
The test for subgroup difference between studies at high risk of bias (that included 183 patients) and studies at low or unclear risk of bias was not statistically significant. A trend towards statistical heterogeneity was evident (I2=13.4%; χ2=1.15, df=1; P=0.28). Sensitivity analysis detected low statistical heterogeneity (highest I2=31.3%) (online supplement). There were no studies with patients with septic shock (online supplement).
Overall with only 2.2% of the required information size, the number needed to treat was 10 patients (95% confidence interval: the number needed to treat is >4 and the number needed to harm is >19) for the comparison of albumin with colloid fluid, excluding studies at high risk of bias. The overall GRADE quality of evidence was judged to be low (table 5).
Discussion
This systematic review and meta-analysis has found that mortality in adults with sepsis, severe sepsis, and septic shock was not significantly reduced or increased by the use of human albumin products as part of fluid volume expansion and resuscitation (with or without improvement of baseline hypoalbuminaemia) in intensive or critical care settings. The point estimates for comparison of human albumin with control fluids (fig 3, table 5) suggested a potential benefit with albumin, indicating a relative risk reduction of −7%, rising to −7.5% with exclusion of studies at high risk of bias from the analysis. For comparison with crystalloid, the point estimates were 6.8% and 7%, respectively (fig 5, table 5). The point estimate for comparison with colloid (fig 7, table 5) was not in favour of human albumin indicating a relative risk increase of 1.6%, but on exclusion of studies at high risk of bias the relative risk reduction was −33.2% in favour of albumin. However, none of these relative risk changes were statistically significant, and so only equivalence between human albumin and comparison groups can be concluded with confidence. The results are generalisable to critically unwell adults with sepsis of any severity. However, extrapolation to other clinical groups where albumin has been used or studied (patients with spontaneous bacterial peritonitis,112 children with malaria,22 or acute respiratory distress syndrome,95 96 98 where the objective is fluid removal) may not be appropriate.
Trial sequential analysis corrected the 95% confidence intervals of the already non-statistically significant point estimates for each human albumin comparison fluid group to account for random error and repetitive testing of accumulating sparse data. For the comparison of albumin with control fluid, the cumulative z score had entered the futility area, suggesting further trials were not required (fig 4). When trials at high risk of bias were excluded, the curve lay just outside the futility boundary but away from both the conventional boundary of benefit (P=0.05) and the trial sequential monitoring boundary of benefit. This was also the case for the comparison of human albumin with crystalloid fluids, whether trials at high risk of bias were excluded or not (fig 6). The information size for the comparison of human albumin with colloid was too low to require futility boundaries.
An acceptable information size was achieved for the comparisons of human albumin with control and crystalloid fluids (85.6% and 80.5% respectively), even with exclusion of studies at high risk of bias (79.9% and 78.9% respectively), on which to draw firm conclusions. However, for the comparison of human albumin with colloid, it was clear the information size was inadequate before (5.8%) and after exclusion of studies at high risk of bias (2.2%); thus firm conclusions cannot be drawn.
Overall our findings were robust to sensitivity, subgroup, meta-regression, and trial sequential analyses (tables 3 and 4, fig 4, fig 6, and online supplement). For the comparison of albumin with control fluids, improved precision (95% confidence interval of 0.85 to 1.00; P=0.06) was observed after exclusion of studies at high risk of bias using a less appropriate fixed effects model that does not account for clinical heterogeneity.41 However, a definite signal of harm with albumin was not observed, consistent with large multicentre studies.7 37 38 104
Our subgroup analysis by sepsis severity did not demonstrate reduced mortality with albumin for any fluid comparison when sepsis was compared to severe sepsis and septic shock (tables 3 and 4; online supplement). However, when patients with septic shock and severe sepsis were analysed in separate subgroups (by separating these groups from ALBIOS38), borderline statistically significant (P=0.05) benefit with albumin was observed overall when albumin was compared with control only after studies at high risk of bias were excluded (online supplement). Albumin was also associated with borderline (P=0.05) reduced mortality compared with crystalloid fluid, but statistical significance was lost when studies at high risk of bias were excluded (P=0.18) (online supplement). However, statistical significance of these comparisons touching the P=0.05 boundary of benefit was not robust to correction with trial sequential analyses, with cumulative z scores crossing futility boundaries (online supplement). Furthermore, no statistically significant benefit was observed individually for any of the sepsis subgroups (including septic shock subgroups), whether studies at high risk of bias were excluded or not. For septic shock subgroups, a borderline trend was evident (P values between 0.06 and 0.10); the relative risk point estimates (0.91 and 0.92; online supplement) moved further in favour of albumin compared with analyses where severe sepsis was combined with septic shock (0.93 and 0.94; tables 3 and 4, online supplement). Nevertheless, the septic shock subgroups were far from the trial sequential monitoring boundary of benefit for the comparisons of albumin with control or crystalloid fluids, with or without retention of studies at high risk of bias (online supplement). No overall effect was observed for the comparison of albumin with colloid, and all studies were at high risk of bias; only 27 patients were in the septic shock subgroup.
No included sepsis randomised trial has reported a statistically significant reduction in mortality associated with albumin. All the patients recruited to EARSS had septic shock, with a median SOFA score 10, but no mortality benefit was observed at 90 days (P=0.94).37 Lack of benefit at this time point (P=0.29) for patients with severe sepsis and septic shock with a median SOFA score of 8 was also reported in ALBIOS.38 However, in a post hoc analysis, reduced mortality (P=0.03) was reported for patients with septic shock at baseline based on cardiovascular SOFA score (vasopressor use), but this did not persist after adjustment for baseline imbalances of clinical relevance, including lactate (P=0.07).38 Survival curves for septic shock patients in both recent European multicentre studies,37 38 which infused 20% albumin and achieved improvement of hypoalbuminaemia to >25 g/L, reported separation after around one week in favour of albumin. The lower baseline mortality of 35.1% in EARSS37 compared with 49.3% in ALBIOS38 might suggest a type 2 error; observed power for ALBIOS for these septic shock patients was 56.7%. Thus the possibility of low information size for the subgroup of septic shock (with or without exclusion of studies at high risk of bias) in our analysis cannot be completely excluded, given the trial sequential analysis cumulative z scores were similarly distant from both the futility boundary and trial sequential monitoring boundary of benefit for albumin comparisons (regardless of study risk of bias; online supplement). Furthermore, SAFE also did not report mortality benefit (P=0.09) for patients with severe sepsis and septic shock, but baseline mortality was 35.3%.7 8 The outcome of the 438 (36.0%) patients with septic shock at baseline based on cardiovascular SOFA (vasopressor use) in SAFE7 8 was not reported, but no difference in cardiovascular SOFA score was observed between albumin and saline treatment groups (P=0.08) and multivariate analysis did not detect an association with death. On this basis, we speculate that patients with septic shock probably did not benefit significantly more than those with severe sepsis. Mortality effect size in our meta-regression analysis did not detect an association with markers of baseline septic shock (vasopressor use and baseline lactate) for any fluid comparison (tables 3 and 4, online supplement). Taken together, large studies at low risk of bias that included patients with septic shock support our subgroup and meta-regression analyses of no statistically robust benefit with albumin.
Our trial sequential analysis models showed that, even with a generous hypothetical 10% relative risk reduction in favour of albumin given to RASP,107 our principal finding of no mortality benefit would remain unchanged (online supplement). The cumulative z score is likely to enter the futility area with smaller relative risk reductions. The information size of the comparison of albumin with control would increase to 93.0% (87.9% if studies at high risk of bias are excluded) and to 92.5% if compared with crystalloid (91.6% if studies at high risk of bias are excluded). However, we await the actual primary outcome data of all-cause mortality at 28 days when the trial is completed. Exploratory models with inclusion of CRISTAL61 also did not support benefit with albumin (online supplement), particularly as the point estimate for this trial was in the direction of harm (relative risk 1.07; 95% confidence interval 0.69 to 1.67).61 However, these are hypothesis generating models and reliable conclusions cannot be based on these analyses alone.
Strengths and weaknesses in relation to other studies
The lack of robust statistically significant survival benefit with human albumin in this analysis is consistent with large randomised trials designed to assess the outcome of all-cause mortality in comparison to crystalloid fluids,7 37 38 and previous meta-analyses studying adults with sepsis,22 113 or severe sepsis with or without septic shock.35 Survival advantage with human albumin for heterogeneous populations in critical or intensive care settings3 with hypoalbuminaemia or hypovolaemia has also not been demonstrated in meta-analyses of randomised clinical trials.4 Thus our analysis is consistent with published literature, and the addition of previously un-pooled 90 day mortality data from ALBIOS38 comprising 43.2% new patient information has not altered the conclusion of no survival benefit. Our exploratory models of RASP107 and CRISTAL,61 added 976 patients for analysis that was consistent with no overall benefit (online supplement).
In contrast to our conclusion, benefit of human albumin was reported in a regression analysis of available severe sepsis patient data from SAFE.8 However, as 24.5% of patients did not have available covariate data, sampling bias may partly account for the observed benefit, which of course loses the advantages of initial randomisation. Patients in SAFE7 8 also did not benefit from the subsequent launch of the management guidelines from the Surviving Sepsis Campaign,110 111 making the results difficult to generalise to current practice. A meta-analysis that combined children with malaria and adults with sepsis reported reduced mortality associated with human albumin (P=0.05).22 However, this borderline association23 was most dependent on SAFE7 (P=0.31 with exclusion of SAFE) and was not robust to a random effects model22 that considers clinical heterogeneity (P=0.08)114 nor to separate analysis of adults with sepsis (odds ratio 0.84; 95% confidence interval 0.69 to 1.02; P=0.08).22 Random error, small study effect,55 56 sparse data, and low information size are likely to have contributed to overestimation of treatment effect size in meta-analyses in critical or intensive care settings. Our analysis has overcome some of these limitations: large information size, inclusion of large recent studies, and trial sequential analysis correction for random error with accumulating data and repetitive testing.70 71 72 73
Our predefined subgroup analysis did not find a difference between hypooncotic (4-5%) albumin and hyperoncotic (20%) albumin for the comparisons of albumin with control, crystalloid, or colloid fluids (table 3 and online supplement). These findings are in contrast to those of CRYCO,115 a retrospective observational cohort study of 1013 patients of whom 384 had sepsis and 105 received hyperoncotic albumin, which reported increased mortality and renal morbidity. In addition a meta-analysis22 reported subgroup difference (P=0.09) between 383 patients who received hyperoncotic albumin and 1594 who received hypooncotic albumin. A confirmatory large randomised clinical trial is often required to confirm the results of a meta-analysis, particularly if the findings are from subgroup analyses.116 EARSS37 and ALBIOS38 confirm that excess mortality was not observed compared with crystalloid in 2602 adults with severe sepsis and septic shock; the requirement for renal replacement therapy was also not statistically different between treatment groups.
Safety of pooled human albumin solutions has not been definitively proven in our analysis. However, trial sequential analysis with data of moderate or high GRADE quality of evidence (table 5) showed that for further studies to eventually show human albumin to be harmful the cumulative z score would have to cross the futility boundary and then the conventional boundary of harm before touching the corrected monitoring boundary of harm (figs 4 and 6). Supporting this notion of likely safety, SAFE recruited 6997 heterogeneous patients and reported overlapping Kaplan-Meier survival curves; and further reassurance comes from EARSS and ALBIOS.7 8 37 38 Furthermore, reassurance of the long term safety of pooled human albumin solutions comes from serious adverse event reporting and epidemiology data,117 118 which found no deaths or transmission of viral or prion disease119 attributed to human albumin. However, the possibility cannot be completely excluded.
Inclusion of trials with inadequate follow-up may have prevented detection of a difference between groups (type 2 error). Only ALBIOS38 and EARSS37 reported 90 day mortality (table 2), the recommended minimum follow-up period for any clinical trial evaluating therapy for sepsis.39 However, SAFE7 8 hospital and 28 day mortality were the same. In our analysis there was also no subgroup heterogeneity evident for timing of mortality observation (table 3 and online supplement). Inadequate follow-up was most problematic for the comparison of albumin with colloid fluid, where all the studies were small and most reported mortality in the intensive or critical care unit (table 2).
Our analysis of human albumin compared with colloid had relatively few patients and was dominated by studies of hydroxyethyl starch (fig 7). Indirectness is a limitation for this comparison in light of the recent rulings by the US Food and Drug Administration24 and European Medicines Agency25 that restrict hydroxyethyl starch use in the US and Europe, making the comparative assessment less relevant to practising healthcare professionals. The literature of hydroxyethyl starch has also been affected by over 90 retractions,120 121 research miscount bias, time bias, and author bias (J Boldt).31 32 33 34 Four studies of 116 patients (comprising 2.8% of the patients included in this study) reported by Boldt et al met our inclusion criteria for this analysis and have not been investigated for research misconduct.34 In contrast to a recent meta-analysis of hydroxyethyl starch use,31 author bias (Boldt et al) was not present in subgroup analysis (online supplement); this is consistent with a 1729 patient meta-analysis studying albumin.113 However, research misconduct and duplicate publication bias was only present in studies of hydroxyethyl starch (online supplement), and a trend towards subgroup heterogeneity, categorised as low (I2=33.0-38.6%), was not found only for the comparison of albumin with crystalloid (tables 3 and 4, online supplement). Interestingly, there was also subgroup heterogeneity between 6% tetrastarch 130 kDa and other hydroxyethyl starch compounds (I2=26.3%), perhaps this may be partly related to time bias where heterogeneity was also present (I2=38.1%). Overall, firm conclusions on comparisons of human albumin with hydroxyethyl starch,5 122 or gelatin, another synthetic colloid of unproven efficacy and safety,12 62 63 cannot be drawn because of sparse data.
Implications for healthcare professionals
We have shown that pooled human albumin solutions did not significantly reduce mortality in adults with sepsis, severe sepsis, and septic shock using currently available and emerging patient information after correction with trial sequential analysis (figs 3–7, online supplement). The possibility of marginal benefit in some sepsis severity groups, particularly septic shock, was not robust to sensitivity analyses. Our GRADE quality of evidence summary tables will assist prescribers and policymakers (table 5). We have also shown that a currently registered but incomplete study (RASP107) is unlikely to alter this finding after trial sequential analysis correction even if a 10% relative mortality benefit is eventually reported (online supplement). The safety of human albumin was implied in our analysis but cannot be concluded with total certainty: the information size for this finding was acceptable (figs 4 and 6).
Although robust evidence for survival advantage in subgroup and meta-regression analyses was not observed with human albumin—even in patients with septic shock (tables 3 and 4; online supplement) or in studies describing early infusion, those that mandated hypoalbuminaemia as an entry criterion, or that reported improvement of hypoalbuminaemia (table 2)—clinicians may still choose to infuse human albumin to raise albumin levels,20 perhaps to reduce morbidity19 or for other clinical reasons not analysed here. Our meta-regression analysis did not detect a relationship with effect size of albumin exposure or serum albumin either before or after treatment (tables 3 and 4, online supplement). Direct relation to clinical patient benefit remains unclear, but other surrogate outcomes might be improved with albumin: increased colloid oncotic pressure,80 81 83 86 87 102 rapid achievement and maintenance of central venous pressure target,8 38 extracellular fluid volume expansion in excess of the infused albumin fluid volume,8 38 89 greater cardiac response to fluid,85 86 cessation of vasopressors one day earlier,37 38 improvement in organ function,19 38 antioxidant function, and sustained thiol levels.89 123. Given the considerable cost of human albumin in comparison with alternatives124 and the lack of effect on mortality, we speculate that it is unlikely the use of human albumin would be supported by a contemporary cost effectiveness analysis in the UK National Health Service, although this may not be the case for insurance based healthcare systems.
Strengths and weaknesses of the study
A major strength of this systematic review was the use of robust Cochrane methodology recommendations (although our study was not registered),41 43 and meta-analysis further challenged with trial sequential analysis to correct for random error and repetitive testing, which often is biased towards an intervention.70 71 72 73 Prominent focus on study bias and quality of evidence was maintained throughout the analysis using GRADE.15 Publication bias and statistical heterogeneity were not present. Predefined sensitivity, subgroup, meta-regression, and trial sequential analyses that included assessment of bias and clinically relevant groups were presented to aid healthcare professionals to make clinical decisions. This analysis was performed promptly with emerging 90 day ALBIOS38 and EARSS37 patient information on mortality outcome, comprising 62.1% of the patients within the analysis.
Subtle underlying bias of the trials included remains a possible limitation of this and any systematic review. We accounted for bias by excluding studies at high risk. However, non-statistically significant heterogeneity, categorised as low, between studies at high risk, which mainly comprised studies with research misconduct or duplicate publication bias, and those at low or unclear risk of bias, was present for the comparisons of human albumin with control or colloid fluids and represented only around 150 patients (online supplement). Clinical heterogeneity will remain within any meta-analysis (tables 1 and 2, online supplement), and we accounted for this by using the more conservative random effects model, which assumed that individual studies were estimating different but related treatment effects. The acceptable information size for the comparison of human albumin with control or crystalloid fluid provides further confidence in the findings.
Unanswered questions and future research
Human albumin solutions are manufactured from pooled plasma donations that are often presented in saline (sodium and chloride 130–160 mmol, with potassium (<2 mmol), sometimes trace aluminium) and have evolved over time. There is also worldwide variation between manufacturers, manufacturing standards (including pathogen inactivation and leucodepletion), use of stabilisers (caprylic acid, N-acetyl-DL-tryptophan, octanoate), with oxidation and post-translational alterations.125 126 However, clear clinical impact of these factors has not been demonstrated. It should be noted that the effect of recombinant human albumin has not been studied in this analysis.
Our findings seem to be consistent, even with the inclusion of our models of the ongoing RASP107 or published CRISTAL61 trials, which do not show the cumulative z curve crossing the trial sequential monitoring boundary of benefit (online supplement). A large randomised clinical trial may be important to confirm our meta-analysis findings, perhaps in adults with septic shock.116 PRECISE97 127 is a randomised double-blinded pilot study of early septic shock treatment with 5% albumin compared with crystalloid (saline) in emergency departments as well as critical or intensive care units; a larger follow-on trial may be registered in the future. Our analysis for the comparison of albumin with colloid fluids was small and unable to draw firm conclusions, and may benefit from further studies of available licensed synthetic colloid solutions, such as gelatin,12 which was infused into only six patients in this analysis.
Conclusion
In this analysis, human albumin solutions as part of fluid volume expansion and resuscitation for adults with sepsis of any severity (with or without baseline hypoalbuminaemia), was not effective at reducing all-cause mortality. Albumin in this setting seems to be safe, as a signal towards harm was also not detected, but this analysis does not support a recommendation for use in sepsis.
What is already known on this topic
Pooled human albumin as part of fluid volume expansion and resuscitation is supported by the Surviving Sepsis Campaign, mainly on the basis of a 2011 meta-analysis that reported reduced mortality in children with malaria and in adults with sepsis, and a subgroup regression analysis of 75.5% of the adults with severe sepsis enrolled into the SAFE trial of 2004, in which early goal directed therapy was not part of the protocol
What this study adds
This systematic review and meta-analysis with trial sequential analysis evaluated mainly (62.1%) new patient information on 90 day mortality from the EARRS and ALBIOS studies
As part of fluid volume expansion and resuscitation (with or without improvement of baseline hypoalbuminaemia), pooled human albumin solutions did not reduce all-cause mortality in adults with sepsis of any severity, including septic shock, in the critical or intensive care setting
A signal towards harm was not detected. GRADE quality of evidence was moderate for comparison with control fluids, high with crystalloids, and very low with colloids (mainly hydroxyethyl starch)
Contributors: AP had the idea, then planned and conducted the study with SJB, MAL, and UW. AP and SJB performed the literature search and selected studies, AP and UW extracted study data, AP and MAL assessed risk of bias, AP performed statistical analysis and wrote the manuscript. All authors assisted in formulation of the research question, assessed quality of evidence, contributed to and developed the final manuscript, and had full access to all of the data.
Funding: This research was not directly funded. AP is funded by the Medical Research Council (MRC) Chain-Florey Fellowship scheme based at the Clinical Sciences Centre, Imperial College London. All authors are supported by the National Institute for Health Research (NIHR) Biomedical Research Centre based at Imperial College Healthcare NHS Trust and Imperial College London. The views expressed are those of the authors and not necessarily those of the NHS, NIHR, or Department of Health. The research and authors are independent of funders.
Competing interests All authors have completed the ICMJE uniform disclosure form at www.icmje.org/coi_disclosure.pdf and declare: no support from any organisation for the submitted work; no financial relationships with any organisations that might have an interest in the submitted work in the previous three years; no other relationships or activities that could appear to have influenced the submitted work.
Ethical approval: Not required.
Transparency The lead author (the manuscript’s guarantor) affirms that the manuscript is an honest, accurate, and transparent account of the study being reported; that no important aspects of the study have been omitted; and that any discrepancies from the study as planned (and, if relevant, registered) have been explained.
Data sharing: No additional data available.
Cite this as: BMJ 2014;349:g4561
Web Extra. Online data supplement as supplied by the author
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