Abstract
This study aimed to review and quantitatively analyze (1) the association of aplastic anemia (AA) with human leukocyte antigen (HLA)-DRB1*15 and HLA-DRB1*15:01 polymorphisms and (2) the association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to immunosuppressive therapy (IST) in AA. Published studies have reported conflicting and heterogeneous results regarding the association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to IST in AA. The PubMed, Embase, Cochrane Library, China National Knowledge Infrastructure, Chinese BioMedical Literature, Wangfang and Chinese Social Sciences Citation Index databases were searched. All relevant publications were searched through December 2015. Odds ratio (OR), risk ratio (RR), and 95% confidence intervals (CI) for the comparison between case–control or cohort studies were evaluated. Finally, 24 articles were identified. For HLA-DRB1*15 and HLA-DRB1*15:01, the OR (95% CI) was 2.24(1.33–3.77), P < 0.01 and 2.50(1.73–3.62), P < 0.01, respectively; and the overall pooled RR was 1.72 (1.30–2.29), P < 0.01 and 1.59 (1.29–1.96), P < 0.01, respectively. Statistical evidence showed no publication bias (P > 0.05). Sensitivity analyses revealed that the results were statistically robust. The meta-analysis suggested that HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms might be associated with increased AA risk in Asians. IST might be more effective in HLA-DRB1*15+ and HLA-DRB1*15:01+ Asian patients with AA than in HLA-DRB1*15− and HLA-DRB1*15:01− Asian patients with AA. Future studies with adequate methodological quality on gene–gene and gene–environment interactions and gene treatment may yield valid results.
Introduction
Aplastic anemia (AA) is a rare, life-threatening hematopoietic stem cell disorder characterized by peripheral blood cytopenia and bone marrow hypoplasia. The prevalence of AA seems to vary in different regions of the world with an annual incidence of two cases per million in Western countries, but a little higher estimated four to seven cases per million in East Asia [1].
A large amount of laboratory and clinical data suggest that immune-mediated destruction of hematopoiesis by activated cytotoxic T cells plays an important role in the pathogenesis of AA. The mechanism of activation of cytotoxic T cells is uncertain, but several potential factors related to antigen recognition, susceptibility of immune response, and secretion of cytokines might be involved. Certain human leukocyte antigen (HLA) alleles were suggested to play a role in the activation of autoreactive T-cell clones in patients with AA [2]. Till date, potential roles of HLA-DRB1 polymorphisms have been postulated in many types of autoimmune diseases (e.g., systemic lupus erythematosus and lupus nephritis[3], rheumatoid arthritis[4]). As with most autoimmune diseases, AA is genetically associated with alleles of the HLA [5–19].
Conflicting reports exist regarding the correlation of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with AA. Dhaliwai et al. (2011) demonstrated a significant association of HLA-DRB1*15 polymorphisms with AA, and the odds ratio (OR) was 11.09 [9]. However, Sun et al. (2004) reported that HLA-DRB1*15 polymorphisms had no significant association with AA [16]. Unfortunately, no report about AA risk exists in genome-wide association studies. The present study was perhaps the first meta-analysis discussing the relationship of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to immunosuppressive therapy (IST) in AA.
Patients with AA have been treated with IST and hematopoietic stem cell transplantation [1, 2]. However, a lack of HLA-matched sibling donors and the cost of transplantation result in most patients with AA tending to accept IST. IST contains cyclosporin (CsA), antithymocyte globulin (ATG), and antilymphocyte globulin (ALG) [1, 2, 20]. In addition, androgen and traditional Chinese medicine (TCM) also showed some effect on AA [21, 22]. A number of conflicting studies have reported different responses to IST in AA with HLA-DRB1*15 and HLA-DRB1*15:01 or without HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms [14–15, 17–18, 23–31]. When the source of hematopoietic stem cell transplantation is limited, it would be very helpful to predict which patients would benefit from IST.
As many conflicting reports were relatively small in sample size, this study increased the statistical power and evaluated evidences from various studies by summarizing them quantitatively using a meta-analytic approach, to obtain a reliable conclusion. The present study aimed to examine (1) the relationship between HLA-DRB1 polymorphisms and AA and (2) the association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to IST in AA.
Material and Methods
This study was performed following the Quality of Reporting of Meta-analyses guidelines [32] and the recommendations of the Cochrane Collaboration [33]. A protocol for this systematic review was published in PROSPERO with the registration number CRD42015032293(S1 File).
Search strategy
This study was performed according to the standards of the Preferred Reporting Items for Systematic Reviews and Meta-analyses (PRISMA) criteria [34]. Several databases (PubMed, Embase, Cochrane Library, China National Knowledge Infrastructure, Chinese BioMedical Literature, Wangfang, and Chinese Social Sciences Citation Index databases) were searched through December 2015 for all reports on the association between HLA polymorphism and AA. The search terms were as follows: (‘‘aplastic anemia”) and (‘‘HLA” or ‘‘human leukocyte antigen” or “DRB1” or ‘‘major histocompatibility complex” or ‘‘MHC”) and (“cyclosporine” or “antilymphocyte serum” or “immunosuppression” or “antirejection therapy” or “antithymocyte globulin”) (S2 File). No language limitations were used in the search. In addition, references of retrieved reports were also searched, and the study authors were contacted by e-mail to identify additional studies and provide missing data.
Inclusion and exclusion criteria
The inclusion criteria were as follows: (1) case–control or cohort study, (2) studies concerned with the associations of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with AA or the association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to IST in AA, (3) sufficient data on complete response (CR) and partial response (PR) stratified by HLA-DRB1*15 and HLA-DRB1*15:01 status, and (4) studies providing sufficient data for estimating OR or a risk ratio (RR) with a 95% confidence interval (CI).
The exclusion criteria were as follows: (1) reviews, comments, editorials, basic science, or animal studies; (2) studies that did not reveal genotype frequency, or in which the relevant data could not be obtained after contacting with the authors, and (3) duplicate studies.
Study selection
The titles and abstracts were examined by two reviewers authors (S Liu and DJ Wu) independently to select eligible studies. Full-text reports of potentially relevant studies were retrieved. When data were overlapped or even duplicated, only the most recent data were included. Full texts were independently examined to decide which articles met the inclusion criteria. Discrepancies in study selection were resolved by a third reviewer (CH Ji).
Data extraction
Data extraction was conducted by two investigators (S Liu and Q Li) independently using a predetermined extraction form. The third participant (CH Ji) was consulted for discussion to reach an agreement concerning discrepancies. The following items were extracted from each article: first author’s last name, publication year, country, number of cases and controls in case–control studies or number of cases in cohort studies, gene-detection method, genes involved, frequency of HLA-DRB1 alleles, sex (M/F), age, treatment method, does, follow-up time, response criteria, and Newcastle–Ottawa Scale (NOS).
The outcome was OR in case–control studies and RR in cohort studies. OR was defined as how strongly the presence of HLA-DRB1*15 and HLA-DRB1*15:01 alleles in patients with AA was associated) with the presence of HLA-DRB1*15 and HLA-DRB1*15:01 alleles in controls. RR was used to show the ratio of probability of the objective response rate (ORR) in patients with HLA-DRB1*15 and HLA-DRB1*15:01 alleles to the probability of the ORR in patients without HLA-DRB1*15 and HLA-DRB1*15:01 alleles. The ORR was defined as the sum of CR and PR.
Quality assessment for individual studies
The study used a scoring system based on the NOS to determine the quality of each article [35]. The NOS ranged between zero (worst) and nine stars (best). Disagreements were settled as described in the preceding section.
Statistical analysis
All statistical analyses were performed using Stata 12.0 (Stata Corporation, TX, USA). Dichotomous data were reported as OR or RR (calculated using the chi-square test). The pooled OR or RR together with the 95% CI used for assessing the strength of association was determined using the Z test. Heterogeneity across studies was checked using the Cochran’s Q statistic and the I2 test [36]. When P value greater than 0.10 for the Q test served as no statistical evidence for heterogeneity, the fixed-effects model was used (shown as “M-H”) [37]; otherwise, random-effects model was used (shown as “D+L”) [38]. Subgroup analyses were performed by regions or drugs. To evaluate the stability of outcomes, a sensitivity analysis was performed by sequential omission of individual studies. Harbord’s test was conducted to evaluate the publication bias, with P less than 0.05 considered statistically significant [39]. When studying the association of HLA-DRB1*15 or HLA-DRB1*15:01 polymorphisms with AA, meta-regression was used to reveal whether age, region or NOS score could lead to heterogeneity.
Results
Study characteristics
The present study met the PRISMA statement requirements (Fig 1 and S1 Table). A total of 1576 published studies were found examining the relationship between HLA polymorphisms and AA. A total of 68 articles were deemed relevant through reading titles and abstracts. Of these, 44 articles were excluded after reading the full text. Finally, 24 articles involving 14 case–control studies and 13 cohort studies were included. Fourteen case–control studies consisted of 938 cases and 5992 controls. Thirteen cohort studies consisted of 609 AA. Tables 1 and 2 list the included studies and their main characteristics. The area of these studies included Asia countries (Japan, Korea, China, Turkey, Malaysia, and Pakistan), Mexico, and Russia. The average score of NOS was 5.6 and 5.3 in case–control and cohort studies, respectively, which revealed that the methodological quality was of average level.
Fig 1. Flow diagram of the study selection process.
Table 1. Characteristics of studies included in the meta-analysis (case–control).
| No. | Authors | Year | Country | Numbers | Sex (M/F) | Age | Controls | Detection methods | NOS | Genes | |||
|---|---|---|---|---|---|---|---|---|---|---|---|---|---|
| Cases | Controls | Cases | Controls | Cases | Controls | ||||||||
| 1 | Song | 2008 | Korea | 109 | 800 | 51/58 | 769/31 | 22 (1–80) | 23 (18–50) | Healthy | PCR-SSP | 6 | *15:01 |
| 2 | Sugimoria | 2007 | Japan | 140 | 491 | 65/75 | – | 60 (12–92) | – | Healthy | PCR-SSP | 6 | *15:01 |
| 3 | Huo | 2011 | China | 115 | 2264 | 70/45 | – | – | – | Healthy | PCR-SSP | 5 | *15 |
| 4 | Liang | 2007 | China | 82 | 400 | 56/26 | – | 2–39 | – | Healthy | PCR-SSP | 6 | *15:01 |
| 5 | Wang | 2014 | China | 43 | 200 | 24/19 | 101/99 | 40 (18–52) | 34 (16–60) | Healthy | PCR-SSP | 6 | *15:01 |
| 6 | Yanga | 2002 | China | 45 | 24 | 28/17 | – | 22 (8–55) | – | Healthy | PCR-SSP | 5 | *15:01 |
| 7 | Sun | 2004 | China | 59 | 30 | 30/29 | 16/14 | 31 (10–58) | 30 (15–60) | Healthy | PCR-SSP | 6 | *15 |
| 8 | Dhaliwal | 2011 | Malaysia | 33 | 109 | 20/13 | – | 18 (13–75) | – | BM donor and Healthy | PCR-SSP | 5 | *15:01 |
| 9 | Rehman | 2009 | Pakistan | 61 | 200 | 39/22 | 111/89 | 17 (1–48) | – | Healthy | PCR-SSP | 6 | *15 |
| 10 | Wang | 2014 | China | 96 | 600 | 56/40 | – | 19 (6–53) | – | BM donor | PCR-SSP | 6 | *15:01 |
| 11 | Fernandez-Torres | 2012 | Mexico | 36 | 201 | 23/13 | 105/96 | 11.7 (0.5–63) | – | National Donor | PCR-SSP | 6 | *15 |
| 12 | Huanga | 2007 | China | 40 | 107 | 26/16 | – | 9 (2–14) | – | Healthy | PCR-SSP | 5 | *15 |
| 13 | Kapustin | 2001 | Russia | 44 | 100 | 27/17 | – | 21 (4–50) | – | Healthy | PCR-SSO | 5 | *15:01 |
| 14 | Yari | 2008 | Iran | 35 | 466 | – | 19 (5–55) | Healthy | PCR-SSP | 5 | *15 | ||
BM,bone marrow;PCR-SSO, polymerase chain reaction with sequence-specific oligonucleotide; PCR-SSP, polymerase chain reaction with sequence-specific primer.
a It is included in the cohort study analysis.
Table 2. Characteristics of studies included in the meta-analysis (cohort study).
| No. | Authors | Year | Country | AA Numbers | Sex(M/F) | Age | Treatment method | Does | Follow-up time(M) | Detection methods | Response criteria | NOS | Genes |
|---|---|---|---|---|---|---|---|---|---|---|---|---|---|
| 1 | Song | 2010 | Korea | 37 | 19/18 | 35(3–66) | CsA+ATG/ALG | - | 6 | PCR-SSP | Champlin | 6 | *15:01 |
| 2 | Sugimori | 2007 | Japan | 77 | – | – | CsA+ATG | CsA: 6mg/kg/d,1y; then 150–250 ng/ml, >6 m; ATG:15mg/kg/d, 5d | 6 | PCR-SSP | Camitta | 6 | *15:01 |
| 3 | Yang | 2002 | China | 26 | - | 22(8–55) | CsA+androgen | - | 3 | PCR-SSP | Zhang | 5 | *15:01 |
| 4 | Huang | 2007 | China | 40 | 24/16 | 9(2–14) | CsA/CsA + ATG +MP | - | 6 | PCR-SSP | Camitta | 5 | *15 |
| 5 | Qiao | 2010 | China | 40 | 22/18 | 36 (11–79) | CsA | CsA: 5mg/kg/d; then 2.5–3 mg/kg/d | 6 | PCR-SSP | Zhang | 6 | *15:01 |
| 6 | Tang | 2002 | China | 29 | 9/20 | 24 (12–55) | CsA+androgen+TCM | CsA:6mg/kg/d,10 d;then 3mg/kg/d, >3 m | 3 | PCR-SSP | – | 5 | *15:01 |
| 7 | Yang | 2004 | China | 50 | 36/14 | 32(13–45) | CsA+androgen | CsA:5mg/kg/d,3 m; then 2.5 mg/kg/d, 3 m | 6 | PCR-SSO/SSP | Zhang | 6 | *15:01 |
| 8 | Nakao | 1996 | Japan | 111 | 55/56 | 56(10–76) | CsA/ATG | CsA: 4–6 mg/kg/d,then 150-250/ng/ml; or Horse ATG:10 or 15 mg/kg/d,5 d (Institut Melieux); or 10 or 20mg/kg/d,8 d (Upjohn); or rabbit ATG: 2.5 mg/kg/d, 5 d (Institut Melieux); | 4–6 | PCR-SSP | – | 5 | *15:01 |
| 9 | Chen | 2007 | China | 51 | 30/21 | 32(12–79) | CsA + ATG | CsA:5mg/kg/d;then 2.5–3mg/kg/d, >3–4 m | 6 | PCR-SSP | Zhang | 6 | *15/*15:01 |
| 10 | Mu | 2009 | China | 37 | 21/16 | 26 (25–57) | CsA+ATG/ALG | - | 4–26 | PCR-SSP | Zhang | 5 | *15/*15:01 |
| 11 | Yang | 2004 | China | 35 | - | 22(7–55) | CsA+ androgen+TCM | CsA:6mg/kg/d,10 d;then 3mg/kg/d, >3 m | 3 | PCR-SSP | Zhang | 5 | *15:01 |
| 12 | Oguz | 2002 | Turkey | 17 | – | – | CsA+ ATG +MP | - | – | – | – | 4 | *15 |
| 13 | Nakao | 1994 | Japan | 59 | 24/35 | 56(15–76) | CsA | - | 3+ | PCR-SSP | – | 5 | *15:01 |
AA, aplastic anemia; ALG, antilymphocyte globulin; ATG, antithymocyte globulin; CsA, cyclosporine A; MP, methylprednisolone; PCR-SSO, polymerase chain reaction with sequence-specific oligonucleotide; PCR-SSP, polymerase chain reaction with sequence-specific primer; TCM, traditional Chinese medicine.
Quantitative synthesis
Association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with AA
The forest plots in Figs 2 and 3 show the main results of the meta-analysis of associations of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with AA. HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms conferred a significantly increased risk. The analysis of the pooled data of six case–control studies revealed a significant increase in the frequency of HLA-DRB1*15 polymorphism (41.0% in AA compared with 30.7% in controls). A moderate level of heterogeneity (I2 = 69.4%, P < 0.01) was found. A random-effects model was used to calculate OR. The overall OR (95% CI) was 2.24(1.33–3.77) with P < 0.01. For HLA-DRB1*15:01 polymorphism (35.6% in AA compared with 18.6% in controls), a moderate level of heterogeneity existed (I2 = 64.3%, P < 0.01). A random-effects model was used. The overall OR (95% CI) was 2.50(1.73–3.62) with P < 0.01.
Fig 2. Forest plot of HLA-DRB1*15 polymorphism and aplastic anemia.
Fig 3. Forest plot of HLA-DRB1*15:01 polymorphism and aplastic anemia.
The subgroup analysis of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms showed similar results. The OR (95% CI) values of HLA-DRB1*15 and HLA-DRB1*15:01 were 2.00(1.53–2.61) from fixed—effects model (Fig 2) and 2.37 (1.59–3.53) from random—effects model, respectively, for the Asian patients (P < 0.01) (Fig 3).
Response to IST in AA
A summary of the meta-analysis findings on the association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to IST in AA is provided in Figs 4 and 5. The response to IST was significantly higher in HLA-DRB1*15+ patients (84.7%) than in HLA-DRB1*15− patients (49.3%), with no heterogeneity (I2 = 0%, P = 0.715). A fixed-effects model was used for calculating RR. The overall RR (95% CI) was 1.72 (1.30–2.29) (P < 0.01).
Fig 4. Forest plot of relative ratios for overall response rate between HLA-DRB1*15+ and HLA-DRB1*15− patients.
Fig 5. Forest plot of relative ratios for overall response rate between HLA-DRB1*15:01+ and HLA-DRB1*15:01− patients.
For HLA-DRB1*15:01, the response to IST was significantly higher in HLA-DRB1*15:01+ patients (78.4%) than in HLA-DRB1*15:01− patients (47.9%), with a moderate level of heterogeneity (I2 = 52.8%, P = 0.016). A random-effects model was used for calculating RR. The overall RR (95% CI) was 1.59 (1.29–1.96) (P < 0.01).
In the CsA therapy subgroup, an improvement in 33 of 40 HLA-DRB1*15:01+ patients was observed, while the response rate was 48/111 in HLA-DRB1*15:01− patients, with no heterogeneity (I2 = 0%, P = 0.956). A fixed-effects model was used for calculating RR. The overall RR (95% CI) was 1.89 (1.47–2.45) with P < 0.01. In the CsA plus ATG/ALG group, a moderate level of heterogeneity was found (I2 = 52.1%, P = 0.099). A random-effects model was used for calculating RR. The overall RR (95% CI) was 1.53 (1.07–2.20) with P < 0.01. In the CsA + androgen group, no heterogeneity was found (I2 = 52.8%, P = 0.146). A fixed-effects model was used for calculating RR. The overall RR (95% CI) was 3.56 (1.87–6.76) with P < 0.01. In the CsA + androgen + TCM group, there is no significant difference between groups (Fig 5).
Sensitivity analyses
A single report involved in the meta-analysis was removed each time to reflect the influence of the individual dataset on the pooled OR or RR, and the corresponding pooled OR and RR were not materially changed (data not shown), indicating that the results were statistically robust.
Publication bias
The shape of the Harbord’s funnel plot showed a relatively symmetric distribution with no publication bias by statistical evidence (P > 0.05, shown in Fig 6), indicating that the results of this study were statistically robust.
Fig 6. Publication bias plots using the Harbord’s test.
(A) Publication bias plot of HLA-DRB1*15 polymorphism and aplastic anemia. (B) Publication bias plot of HLA-DRB1*15:01 polymorphism and aplastic anemia. (C) Publication bias plot of RR between HLA-DRB1*15+ and HLA-DRB1*15− patients. (D) Publication bias plot of RR between HLA-DRB1*15:01+ and HLA-DRB1*15:01− patients.
Influence of age at diagnosis, region, and NOS score
The results of meta-regression analysis showed that age, region, or NOS score did not account for heterogeneity when studying the association of HLA-DRB1*15 or HLA-DRB1*15:01 polymorphisms with AA (Table 3).
Table 3. Meta-regression.
| HLA-DRB1*15 | HLA-DRB1*15:01 | |||
|---|---|---|---|---|
| β | P-value | β | P-value | |
| Age | -0.093 | 0.067 | -0.001 | 0.919 |
| Region | 1.542 | 0.092 | -0.495 | 0.484 |
| NOS score | 0.098 | 0.912 | -0.784 | 0.103 |
Discussion
This study systematically reviewed the articles on the relationship of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to IST in AA. Based on the search criteria, 24 studies involving 14 case–control studies and 13 cohort studies were included in the final meta-analysis. A total of 938 cases and 5992 controls from case–control studies were used to find the relationship of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with AA in the pooled analyses. Moreover, 609 AA in cohort studies were used to discuss the association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with response to IST in AA. This study was perhaps the first meta-analysis to explore the relationship of DRB1*15 and DRB1*15:01 with response to IST in AA.
Of the six studies about the associations between HLA-DRB1*15 polymorphisms and AA and eight studies about the associations between HLA-DRB1*15:01 polymorphisms and AA, the majority indicated that HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms might be potential risk factors for AA [6–10, 14–15, 18–19, 24], but four studies indicated no association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with AA [5–6, 12–13,16]. The pooled results of the meta-analysis were consistent with most studies, which indicated HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms as potential risk factors for AA (OR = 2.24, 2.50, respectively; Figs 2 and 3). In subgroup analysis, region was the reason for heterogeneity in HLA-DRB1*15 but not in HLA-DRB1*15:01. In addtion, there was only one small non-Asians group in each analysis. So it is more valid to say that these associations were found in Asian populations.
Of the 4 studies about the associations between HLA-DRB1*15 polymorphisms and response to IST in AA and 11 studies about the associations between HLA-DRB1*15:01 polymorphisms and response to IST in AA, the majority indicated that patients with AA who carried HLA-DRB1*15 or HLA-DRB1*15:01 alleles might have a good response rate for the IST [14–15, 23–24, 26–27, 30–31]. Seven studies indicated no association of HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms with IST in AA [17–18, 25, 28–30]. The pooled results showed that the response rate was significantly higher in HLA-DRB1*15+ and HLA-DRB1*15:01+ patients than in HLA-DRB1*15− and HLA-DRB1*15:01− patients (84.7% vs 49.3% and 78.4% vs 47.9%, RR = 1.72 and 1.59, respectively). It means that HLA-DRB1*15+ and HLA-DRB1*15:01+ patients with AA treated with IST were more sensitive than HLA-DRB1*15− and HLA-DRB1*15:01− patients.
In a subgroup analysis, HLA-DRB1*15:01+ patients treated with CsA, CsA + ATG/ALG, or CsA + androgen showed a higher response rate than DRB1*15:01− patients (RR = 1.89, 1.53 and 3.56, respectively). Only two articles included the CsA + androgen subgroup. Hence, the results needed further investigation. A negative result was obtained in CsA + androgen + TCM group. It is known that TCM combine different kinds of herbs that might have cause the clinical heterogeneity. Further researches and analyses are needed to validate the findings.
Heterogeneity is a potential issue that may affect the results of all meta-analyses. Statistical heterogeneity existed among some analyses in the present study. Several methods were applied to examine whether the results were robust. First, we considered region, mean or median age or NOS score as a covariate in the meta-regression analysis. The results indicated that these factors are not statistically significant (P>0.05) for heterogeneity when studying the association between DRB1*15 or DRB1*15:01 polymorphisms and AA. Second, subgroup analyses by region or drugs and sensitivity analyses were performed. It indicated that drug groups led to heterogeneity when studying the association of HLA-DRB1*1501 polymorphisms with response to IST in patients with AA. Additionally, the region was a significant factor for heterogeneity when studying the association between HLA-DRB1*15 polymorphisms and AA. However, the region was not a significant factor for heterogeneity when studying the association between HLA-DRB1*15:01 polymorphisms and AA.
Both English and Chinese language reports were identified, obtained, and included in this analysis to avoid the local literature bias[40]. However, several limitations still could not be ignored. First, the results were based on unadjusted analysis. Some factors such as the dose, product and biological characteristics of the xenoantisera, short telomeres, younger age, absolute reticulocyte count, absolute lymphocyte count, normal cytogenetics, and paroxysmal nocturnal hemoglobinuria clone, were also associated with a higher response rate [1, 41]. However, information was not available to perform more detailed analysis. As a result, these factors were not considered in this study. Further researches are still needed in the future to figure out the complex effect of the aforementioned factors and HLA-DRB1*15, and HLA-DRB1*15:01 polymorphisms. Second, HLA typing was performed by PCR with sequence-specific primers in most included articles, but two reports involved PCR with sequence-specific oligonucleotide primers. The typing methods were not identical between different researches, which might have led to the heterogeneity in the present analysis. Third, probably most of the HLA-DRB1*15 patients were actually HLA-DRB1*15:01, but it was not confirmed. Finally, because of the low incidence of DRB1 genotype, limited studies were available for inclusion in this meta-analysis. Only few articles were found about other ethnicities. Hence, it could not be concluded whether HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms were different in those ethnic groups.
Conclusions
HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms might be associated with increased AA risk in Asians. IST might be more effective in Asian patients with HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms than in Asian patients without HLA-DRB1*15 and HLA-DRB1*15:01 polymorphisms. More articles with adequate methodological quality on gene–gene and gene–environment interactions and gene treatment may eventually lead to valid results in the future.
Supporting Information
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Acknowledgments
This work was supported by grants from the State Administration of Traditional Chinese Medicine of the People’s Republic of China (No. JDZX2012172), the Administration of Traditional Chinese Medicine of Zhejiang Province (No.2016ZA084). The authors wish to express their sincere thanks to Prof. Hai-Feng Pan for his technical assistance.
Data Availability
All relevant data are within the paper and its Supporting Information files.
Funding Statement
This work was supported by grants from the State Administration of Traditional Chinese Medicine of the People’s Republic of China (No. JDZX2012172), the Administration of Traditional Chinese Medicine of Zhejiang Province (No.2016ZA084). The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
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