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. 2012 Aug 16;16(8):1497–1506. doi: 10.1017/S1368980012003709

Efficacy of oral iron therapy in improving the developmental outcome of pre-school children with non-anaemic iron deficiency: a systematic review

Kawsari Abdullah 1,2, Tetyana Kendzerska 2, Prakesh Shah 2,3, Elizabeth Uleryk 4, Patricia C Parkin 1,2,5,*
PMCID: PMC10271588  PMID: 22894941

Abstract

Objective

To systematically review the efficacy and safety of oral Fe therapy in pre-school children (1–5 years) with non-anaemic Fe deficiency, determined by children's developmental and haematological status and the incidence of reported side-effects.

Design

A random-effects model was used to show mean differences with 95 % confidence intervals of developmental and haematological scores between Fe-treated and non-treated groups.

Setting

MEDLINE, EMBASE, Cochrane library and bibliographies of identified articles were searched up to September 2011. Randomized and observational studies were assessed by two reviewers independently. Quality of the trials was assessed on the basis of concealment of allocation, method of randomization, masking of outcome assessment and completeness of follow-up.

Subjects

From the titles of 743 articles, full text review was completed on forty-six and two randomized trials of acceptable quality met the inclusion criteria. The two trials included a total of sixty-nine children.

Results

One study showed a statistically significant difference in the post-treatment Mental Developmental Index score among children who received oral Fe therapy v. no therapy (mean difference = 6·3, 95 % CI 1·5, 11·0, P value not provided). Both studies showed significant improvement in serum ferritin level (μg/l: mean difference = 51·1, 95 % CI 33·6, 68·6, P < 0·01 and mean difference = 17·1, 95 % CI 7·5, 26·6, P value not provided, respectively) in children who received Fe therapy.

Conclusions

Evidence is insufficient to recommend oral Fe therapy to children with non-anaemic Fe deficiency. There is urgent need of conducting adequately powered, randomized trials examining the efficacy of oral Fe therapy in pre-school children with non-anaemic Fe deficiency.

Keywords: Non-anaemic iron deficiency, Child development, Pre-school children

Iron deficiency (ID) is the most common and widespread nutritional disorder in the world( 1 ). ID represents a spectrum ranging from non-anaemic iron deficiency (NAID: normal Hb, low Fe status) to iron deficiency with anaemia (IDA: low Hb, low Fe status). Because Fe is involved in many central nervous system processes, its deficiency may adversely affect the cognitive performance and motor development in children( 2 – 4 ).

Summarized in two systematic reviews, numerous studies have established a relationship between IDA and poor cognitive and motor development in infants and children( 5 , 6 ). However, there is conflicting evidence as to whether this delay can be reversed following treatment with oral Fe. Most randomized trials have shown that children treated with the recommended dose and duration of Fe have corrected anaemia but biochemical evidence of ID as well as poor cognitive and motor development persist( 7 – 9 ). These findings suggest that ID, when it reaches its most severe stage, may have irreversible effects.

Mild to moderate ID has also been associated with adverse developmental consequences. Observational studies suggest that, compared with children who are Fe sufficient, children with NAID tend to have lower developmental scores, verbal competency, comprehension and intelligence quotient( 8 , 10 , 11 ). However, studies focusing on the efficacy of Fe therapy in children with IDA and also including children with NAID and Fe sufficiency as comparison groups did not show developmental difference between the latter two groups( 7 ). Thus, the severity of ID that may impact the development of children remains unknown. Current WHO and American Academy of Pediatrics guidelines do not recommend screening for NAID( 2 , 12 ). Therefore, children with this condition are less likely to be identified and treated. This further adds to the insufficient evidence base relating NAID as a cause of poor development in children and the efficacy of Fe therapy in this population. Furthermore, it is possible that the relationship between ID and development is confounded by other factors like low socio-economic factors, poor maternal education, low birth weight, early weaning and parasitic infection( 13 – 16 ).

Oral Fe is the treatment of choice for IDA because of its effectiveness, safety and cost-effectiveness( 17 , 18 ). When taking Fe preparations orally, side-effects occur occasionally in the form of staining of teeth, vomiting, heartburn, darkening of stools, constipation or loose stools( 19 , 20 ). Rates of non-compliance attributed to side-effects range from 0 % to 6 %( 21 ).

The current controversy regarding ID in children relates to the degree of ID that impairs child development and the efficacy of Fe therapy in correcting developmental deficits( 22 ). The overall aim of the present evidence synthesis was to determine whether there is enough evidence to suggest that NAID is causally associated with poor development in children and whether oral Fe therapy is effective in improving development in pre-school children with NAID. Considering the irreversible developmental impact of IDA, we hope that this systematic review will focus attention on NAID, the early stage of ID, in order to build an evidence base for screening and treatment of NAID to prevent progression to IDA.

Objectives

The primary objective of the current review was to evaluate the efficacy of oral Fe therapy in children of pre-school age (1–5 years) with NAID, defined as serum ferritin <12 μg/l and Hb > 110 g/l, in improving developmental outcomes. The secondary objectives were to evaluate the efficacy of oral Fe therapy in terms of haematological outcomes and incidence of side-effects of Fe therapy in children of pre-school age (1–5 years) with NAID.

Methods

Criteria for considering studies for review

Types of studies

Randomized or quasi-randomized controlled trials and observational studies with prospective longitudinal design were considered for the current review. Separate meta-analysis for observational studies and randomized controlled trials were planned to avoid methodological heterogeneity.

Types of participants

The participants were Fe deficient (serum ferritin <12 μg/l) but non-anaemic (Hb > 110 g/l) children who were otherwise healthy and aged 1–5 years. Studies on children with developmental disorders, chronic disease, congenital or genetic disorder and ID were excluded.

Types of interventions

The dose and duration of Fe therapy have been established for IDA but not for NAID. According to guidelines for the prevention of IDA and the opinion of experts, it was decided to select studies with a minimal dose of 2 mg elemental Fe/kg body weight per d once daily, administered for a minimum duration of 3 months( 2 , 23 ). The treatment group included children who received oral Fe therapy (≥2 mg elemental Fe/kg body weight per d administered for ≥3 months) with or without other interventions aimed at improving Fe level (such as dietary counselling, vitamin C, folic acid). The control group included children receiving placebo or no treatment.

Types of outcome measures

Primary outcome. The primary outcome for the current review was the change or the end-of-study scores of children's development, measured using any standardized scale that can be converted to standard scores expressed by mean and standard deviation. Bayley's Scale of Infant Development (BSID) is one such scale which has a population mean of 100 and an sd of 15( 24 ).

Secondary outcomes. Secondary outcomes included the change or the end-of-study levels of Hb and serum ferritin. Safety outcomes included the rate of any reported side-effects of Fe treatment including vomiting, heartburn, constipation, loose stools, staining of teeth and darkening of stools.

Search methods for identification of studies

A comprehensive search strategy was performed to identify all relevant studies, including searching the electronic literature and hand searching. We searched the following electronic databases and updated results as of 13 January 2011: MEDLINE (1950 to the present), EMBASE (1980–2011 Week 1) and the Cochrane Controlled Trials Register (CCTR; Cochrane Library issue 4, 2010). We scanned reference lists of identified trials and important review articles for published studies which may have been missed by the literature search. We included only published data in English language. However, we planned to contact key authors of those articles where we expected to find data not published but relevant to our review.

Search terms

Under the supervision of an expert librarian (E.U.), the following key search terms were used: ‘anemia/hypochromic anemia’, ‘iron/blood’, ‘iron-deficiency’ and ‘ferritin’ combined with concepts of child development. Appropriate truncations and possible misspellings were included. Where appropriate, a trials search filter was applied. The described search strategy (detailed search strategy shown in the Appendix) was used for MEDLINE. For use with EMBASE and the Cochrane Library this strategy was adapted slightly.

Data collection and analysis

Selection of studies

Titles and abstracts of studies identified on searches of electronic databases were read to determine whether they might meet the inclusion criteria. Full copies of those possibly meeting these criteria were assessed by two independent reviewers (K.A., T.K.). Studies that met the inclusion criteria were again reviewed by the same reviewers for quality assessment. Differences of opinion about inclusion of studies and quality assessment of studies were resolved by discussion. Arbitration by a third reviewer (P.C.P.) was kept open.

Assessment of risk of bias in included studies

For randomized controlled trials, the two reviewers (K.A., T.K.) independently assessed the methodological quality of the studies using a predefined checklist, as suggested for the Cochrane Database of Systematic Reviews( 25 ). We performed an overall assessment of risk of bias, based on responses from criteria used to assess the quality of the studies. Studies that reached A or B score were intended to be included in the meta-analysis. For studies with longitudinal designs we intended to score the quality of the studies using the Newcastle–Ottawa Scale (NOS)( 26 ). We planned to include studies that had at least one star in each category of the scale. Assessment was intended to be carried out independently by two reviewers.

Data extraction and synthesis

We planned to use the RevMan software version 5·0 to generate meta-analyses and show summarized effect size if appropriate data were available. Data regarding the stated outcomes of the review (standardized mean difference (SMD) or mean difference (MD) with 95 % CI for continuous outcomes and relative risk (RR) with 95 % CI for binary outcomes) were extracted and entered into the RevMan software. The original data were not modified but for the purpose of data synthesis for meta-analysis, calculations were required from available data. Pooled results were to be presented as forest plots. Statistical heterogeneity was assessed using the Cochran Q test and by calculating I 2 values. We expected methodological, clinical and statistical heterogeneity among the studies. Thus, we intended to use the random-effect model for meta-analyses. Subgroup analysis for children aged <2 and ≥2 years was planned. The robustness of the results were intended to be checked by performing sensitivity analysis showing the influence of study quality as well as the influence of large-scale studies. In the case of duplicate publications and companion papers of a primary study, the original publication (usually the oldest version) obtained priority. We intended to assess publication bias using the funnel plot method.

Results

Literature search

Excluding duplicates, 743 articles were identified in first scan; 697 were excluded after reading the titles and abstract (Fig. 1). Full text review was completed on forty-six articles and we identified two randomized clinical trials of oral Fe treatment in which children with NAID were randomized to a treatment or control group( 27 , 28 ). For both studies, the primary objective was to study children with IDA; however, both included children with NAID as a comparison group, and these data were available for the review. No studies with observational design met the inclusion criteria. The reason for exclusion of forty-four studies is reported in Table 1.

Fig. 1.

Fig. 1

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Flow diagram for selection of studies in the current review

Table 1.

Characteristics of studies excluded from the current review

No. Author, date, country Reason for exclusion Citation
1. Aukett et al., 1986, Britain Did not meet Hb inclusion criteria Arch Dis Child 61, 849–857
2. Ayala et al., 2008, Mexico Did not meet Hb inclusion criteria; did not meet age inclusion criteria Nutr Neurosci 11, 61–68
3. Black et al., 2004, Bangladesh Did not meet age inclusion criteria Am J Clin Nutr 80, 903–910
4. Corapci et al., 2006, Costa Rica Follow-up of Lozoff et al., 1987 study J Dev Behav Pediatr 27, 371–378
5. Deinard et al., 1986, USA Did not meet serum ferritin inclusion criteria J Pediatr 108, 681–689
6. Engle et al., 1999, Guatemala Did not meet intervention inclusion criteria Early Hum Dev 53, 251–269
7. Friel et al., 2003, Canada Did not meet NAID definition J Pediatr 143, 582–586
8. Gonzalez et al., 2007, Argentina Did not meet intervention inclusion criteria Biol Trace Elem Res 120, 92–101
9. Gunnarsson et al., 2007, Iceland Did not meet intervention inclusion criteria Acta Paediatr 96, 391–395
10. Harahap et al., 2000, Indonesia Did not meet Hb inclusion criteria Eur J Clin Nutr 54, Suppl. 2, S114—S119
11. Hokama et al., 2005, Japan Did not meet intervention inclusion criteria; did not meet NAID definition Asia Pac J Public Health 17, 19–21
12. Lind et al., 2004, Central Java Did not meet Hb and serum ferritin inclusion criteria Am J Clin Nutr 80, 729–736
13. Lozoff et al., 1982, Guatemala Did not meet NAID definition J Pediatr 100, 351–357
14. Lozoff et al., 1985, Guatemala Follow up of Lozoff et al., 1982 study J Dev Behav Pediatr 6, 69–75
15. Lozoff et al., 1987, Costa Rica Did not include a control group of children with NAID Pediatrics 79, 981–995
16. Lozoff, 1989, Costa Rica Follow up of Lozoff et al., 1987 study Am J Clin Nutr 50, 3 Suppl., 641–651
17. Lozoff et al., 1991, Costa Rica Follow-up of Lozoff et al., 1987 study N Engl J Med 5, 687–694
18. Lozoff et al., 1996, Costa Rica Did not include a control group of children with NAID J Pediatr 129, 382–389
19. Lozoff et al., 1998, Costa Rica Follow up of Lozoff et al., 1987 study Child Dev 69, 24–36
20. Lozoff et al., 2000, Costa Rica Follow up of Lozoff et al., 1987 study Pediatrics 105, E51
21. Lozoff et al., 2003, Chile Did not meet intervention inclusion criteria Pediatrics 112, 846–854
22. Lozoff et al., 2006, Costa Rica Follow up of Lozoff et al., 1987 study Arch Pediatr Adolesc Med 160, 1108–1813
23. Lozoff et al., 2007, India Did not include NAID group J Nutr 137, 683–689
24. Metallinos-Katsaras et al., 2004, Greece Did not include NAID group in analysis Eur J Clin Nutr 58, 1532–1542
25. Olney et al., 2007, Tanzania Did not meet serum ferritin inclusion criteria; did not meet study design criteria (a cross-sectional analysis) J Nutr 137, 2756–2762
26. Otero et al., 2004, Mexico Did not meet age inclusion criteria Clin Neurophysiol 115, 2259–2266
27. Pollitt et al., 1985 A letter to the editor Lancet 9, 158
28. Pollitt et al., 1986, Guatemala Did not include NAID group Am J Clin Nutr 43, 555–565
29. Pollitt, 2001, Canada Not an original study J Nutr 131, 2 Suppl. 2, 669S–675S
30. Pollitt et al., 2002, Indonesia Did not meet healthy child inclusion criteria; did not meet intervention inclusion criteria J Nutr 132, 2617–2625
31. Seshadri et al., 1982, India Did not meet age inclusion criteria Br J Nutr 48, 233–240
32. Shafir et al., 2006, Costa Rica Follow-up of Lozoff et al., 1987 study Hum Mov Sci 25, 821–838
33. Soemantri et al., 1985, Indonesia Did not meet age inclusion criteria; did not include NAID group Am J Clin Nutr 42, 1221–1228
34. Soewondo et al., 1989, Indonesia Did not include a control group of children with NAID Am J Clin Nutr 50, 3 Suppl., 667–673
35. Steinmacher et al., 2007, Germany Did not meet healthy child inclusion criteria; did not meet age inclusion criteria Pediatrics 120, 538–546
36. Stoltzfus et al., 2001, Zanzibar Did not meet intervention inclusion criteria; did not include NAID group BMJ 15, 1389–1393
37. Sungthong et al., 2004, Thailand Did not meet intervention inclusion criteria; did not include NAID group J Nutr 134, 2349–2354
38. Walter et al., 1983 Did not meet duration and dose of intervention inclusion criteria J Pediatr 102, 519–522
39. Walter et al., 1989, Chile Did not meet duration and dose of intervention inclusion criteria Pediatrics 84, 7–17
40. Walter, 1989, Chile Did not meet duration and dose of intervention inclusion criteria Am J Clin Nutr 50, 3 Suppl., 655–661
41. Yalcin et al., 2000, Turkey Did not meet age inclusion criteria Pediatr Int 42, 625–630
42. Corapci et al., 2010, Costa Rica Follow-up of Lozoff et al., 1987 study J Pediatr Psychol 35, 296–305
43. Gupta et al., 2010, India Did not include NAID group Indian J Pediatr 77, 375–359
44. Lozoff et al., 2010, Chile Did not meet age inclusion criteria; did not meet intervention criteria Pediatrics 126, e884–e894
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NAID, non-anaemic iron deficiency.

Study participants and interventions

The baseline characteristics of the children in the two included studies and the dosage and duration of oral Fe treatment are reported in Table 2. Both studies used the same inclusion criteria: birth weight greater than 2500 g; singleton; no major congenital anomalies; no jaundice treated by phototherapy; no hospital admission or supplementation with micronutrients during the 6 months before enrollment; no clinically identified neuromotor delay; no chronic illness or folic acid deficiency; no signs of abnormal haemoglobinopathy or thalessaemia; and weight, length and head circumference within ±2 sd of reference standard.

Table 2.

Characteristics of studies included in the current review

Author, date, country Study design Participants Exclusion criteria Interventions, dosage, duration Outcome measures Side-effects Adjusted covariates Drop-out Findings
Akman et al., 2004, Turkey Single-blind RCT Children aged 6–30 months (108 in total); NAID (n 40); treatment (n 21); control (n 19) Pervasive developmental disorder or severe mental and motor disability Oral ferrous-glycine-sulfate therapy (3 mg/kg per d, twice daily); 3 months BSID-I (MDI and PDI) NR Unclear Among the total participants the parents of four children declined to participate and two others dropped out during follow-up MDI score differences between the NAID treatment and control groups were found to be significant after 3 months of oral Fe treatment. Similar findings were not found for the PDI score
Idjradinata et al., 1993, Indonesia Double-blind RCT Children aged 12–18 months (141 in total); NAID (n 29); treatment (n 14); control (n 14) Hb between 105 and 120 g/l Oral ferrous sulfate (3 mg/kg per d); 4 months BSID (MDI and PDI) NR Mothers’ maximum school grade Among the total participants the parents of fifteen infants declined to participate Pre-treatment to post-treatment changes in the two intervention subgroups within the NAID group were not significantly different
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RCT, randomized controlled trial; NAID, non-anaemic iron deficiency; BSID, Bayley Scales of Infant Development; MDI, Mental Developmental Index; PDI, Psychomotor Developmental Index; NR, not reported.

Both the studies had the same inclusion criteria.

Akman et al. (2004, Turkey) included 108 children aged 6–30 months (average age 17 months)( 28 ). Of these, forty (37 %) had NAID; twenty-one received oral Fe treatment and nineteen received no treatment. Oral Fe was given for 3 months at a dose of 3 mg elemental Fe/kg body weight per d, twice daily. The Hb and serum ferritin cut-offs were: IDA (Hb < 11 g/dl, serum ferritin ≤12 μg/l, mean corpuscular volume <70 fl) and NAID (Hb ≥ 11 g/dl, serum ferritin ≤12 μg/l, mean corpuscular volume ≥70 fl). Idjradinata et al. (1993, Indonesia) included 141 children aged 12–18 months( 27 ). Of these, twenty-nine (21 %) had NAID; fourteen received oral Fe treatment and fifteen received no treatment. The oral Fe was given for 4 months at a dose of 3 mg of elemental Fe/kg body weight per d. The Hb and serum ferritin cut-offs were: IDA (Hb < 105 g/l, transferrin saturation ≤10 % and serum ferritin ≤12 μg/l) or NAID (Hb ≥ 120 g/l, transferrin saturation ≤10 % and serum ferritin ≤ 12 μg/l). Children whose Hb level was between 105 and 120 g/l were excluded.

Methodological quality

The results of the assessment of the risk of bias of the two included studies are reported in Table 3. Both studies showed moderate risk of bias (B quality). Both studies provided insufficient information regarding allocation concealment. Akman et al. (2004, Turkey) was a single-blind trial; mothers were not blinded because placebo was not used. Further, although the two groups differed in a number of variables, for example sociodemographic variables, it was not clear whether the analysis was adjusted for these differences. Idjradinata et al. (1993, Indonesia) did not report on the method of laboratory analysis. Both studies reported child development using the BSID. This scale reports development using two indices, the Mental Developmental Index (MDI) and the Psychomotor Developmental Index (PDI), with the standardized score having a mean of 100 and an sd of ±15.

Table 3.

Risk of bias table (quality assessment of included studies)

Author, date, country Sequence generation Allocation concealment Blinding of participants, personnel and outcome assessors Incomplete outcome data Selective outcome reporting Other bias ABC Cochrane score
Akman et al., 2004, Turkey Adequate (table of random numbers) Unclear (no information was provided) Inadequate (a trained psychologist, unaware of each child's haematological status, administered the BSID-I to all children before and after the 3-month follow-up; mothers were not blinded due to placebo not being used) Adequate (number and reasons for drop-outs and withdrawals were described) Adequate (the IDA group was the main focus) Unclear (adjustment for other biases) B – moderate risk of bias
Idjradinata et al., 1993, Indonesia Adequate (table of random numbers) Unclear (no information was provided) Adequate (placebo was a syrup similar in appearance to the ferrous sulfate and both had a sweet, cherry flavour) Adequate (number and reasons for drop-outs and withdrawals, the procedure with compliance were described) Adequate (the IDA group was the main focus) Adequate (adjustment for other biases) B – moderate risk of bias
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BSID, Bayley Scales of Infant Development; IDA, iron-deficiency anaemia.

Outcomes

Meta-analyses were not performed due to high level of heterogeneity (see ‘Heterogeneity and publication bias’ section) between the two studies. Considering the primary outcome, comparison of the MDI and PDI in the Fe-treated and non-treated NAID groups, Akman et al. (2004, Turkey) showed a statistically significant difference in the post-treatment MDI score (MD = 6·3, 95 % CI 1·5, 11·0, P value not provided); and comparison of the post-treatment PDI score showed no statistically significant difference (MD = −0·2, 95 % CI −7·0, 6·6; Figs 2 and 3). Idjradinata et al. (1993, Indonesia) showed no statistically significant difference in either the post-treatment MDI score (MD = −1·6, 95 % CI −9·4, 6·2) or the post-treatment PDI score (MD = 1·2, 95 % CI −6·0, 8·4; Figs 2 and 3).

Fig. 2.

Fig. 2

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Forest plot of comparison: developmental scores (outcome is Mental Developmental Index, MDI) of non-anaemic iron-deficient pre-school children on iron supplementation v. no treatment/placebo; mean differences with 95 % confidence intervals represented by vertical lines (IV, inverse variance). Study results are not combined

Fig. 3.

Fig. 3

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Forest plot of comparison: developmental scores (outcome is Psychomotor Developmental Index, PDI) of non-anaemic iron-deficient pre-school children on iron supplementation v. no treatment/placebo; mean differences with 95 % confidence intervals represented by vertical lines (IV, inverse variance). Study results are not combined

Considering the secondary outcomes, namely the comparison of Hb and serum ferritin levels in the Fe-treated and non-treated NAID groups, Idjradinata et al. (1993, Indonesia) reported a statistically significant increase in the post-treatment Hb level (g/l: MD = 11·5, 95 % CI 5·1, 17·9, P < 0·01) and the post-treatment serum ferritin level (μg/l: MD = 51·1, 95 % CI 33·6, 68·6, P < 0·01; Figs 4 and 5). Akman et al. (2004, Turkey) reported no statistically significant increase in post-treatment Hb level (g/l: MD =2·7, 95 % CI −1·7, 7·1); but the ferritin level showed a significant increase (μg/l: MD = 17·1, 95 % CI 7·5, 26·6, P value not provided; Figs 4 and 5). Neither of the studies intended to report side-effects.

Fig. 4.

Fig. 4

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Forest plot of comparison: haematological outcome (Hb, g/l) of non-anaemic iron-deficient pre-school children on iron supplementation v. no treatment/placebo; mean differences with 95 % confidence intervals represented by vertical lines (IV, inverse variance). Study results are not combined

Fig. 5.

Fig. 5

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Forest plot of comparison: haematological outcome (serum ferritin, μg/l) of non-anaemic iron-deficient pre-school children on iron supplementation v. no treatment/placebo, outcome; mean differences with 95 % confidence intervals represented by vertical lines (IV, inverse variance). Study results are not combined

Heterogeneity and publication bias

Clinical heterogeneity between the studies is described in Table 2. Some of this heterogeneity can be explained by the difference in the range of age of the children in the two studies. The children in Akman et al. were relatively older compared with Idjradinata et al. (mean age, months: 18 (sd 6·1) v. 14 (sd 0·51)). Other potential causes of heterogeneity include the exclusion criteria and duration of Fe treatment (3 months v. 4 months). The drop-out rates for the two studies were approximately 6 % and 11 % (of the total participants). Neither study reported the characteristics of the children who declined to participate. Only Idjradinata et al. reported the results after adjusting for mothers’ maximum school grade and no clear information regarding adjustment for covariates was reported in Akman et al.'s study. When we attempted to combine the results of the two studies, evidence of high statistical heterogeneity was observed. The combined result for the MDI score showed a Q value of 3·51 (P = 0·06) and an I 2 value of 72 %, indicating significant statistical heterogeneity. For the PDI score the Q value was 0·08 (P = 0·8) and the I 2 value 0 %, indicating less heterogeneity. However we were not able to estimate the between-study variance with precision with only two studies because the π 2 (variability) as well as I 2 become 0 when Q ≤ k − 1 (df = 1). Due to the lack of homogeneity between the studies we decided not to show the combined effect size of the results. We are unable to comment on the publication bias issue with only two included studies.

Subgroup and sensitivity analyses

Since only two studies met the inclusion criteria, this restricted us from performing any predefined subgroup or sensitivity analyses.

Discussion

Major findings

In the current systematic review, two randomized controlled trials were identified for children of pre-school age with NAID treated with oral Fe treatment v. no treatment. This limited number of identified studies on NAID shows the need to carry out more research on this very important topic. Furthermore, due to high level of clinical, methodological and statistical heterogeneity we were unable to combine the results of the trials. One study demonstrated a significant difference in the BSID MDI post oral Fe treatment( 28 ). Neither study demonstrated a significant difference in the post-treatment BSID PDI. However, neither study adjusted for pre-treatment development score. Therefore, the efficacy of oral Fe therapy in children with NAID to improve developmental outcome remains in question.

For the haematological outcomes, both studies demonstrated a significant improvement in the post-treatment serum ferritin levels. One demonstrated a significant improvement in the post-treatment Hb level( 27 ). The other study, despite demonstrating a significant improvement in post-treatment serum ferritin level, did not demonstrate a significant difference in post-treatment Hb level( 28 ). A possible explanation for this finding is that these children may have had very mild ID. It has been shown in therapeutic trials of Fe treatment that children with greater ID respond to Fe treatment at a higher rate (increase of Hb 10 g/l is indicative of ID)( 29 ).

Limitations

Several methodological and statistical issues lead to the finding that both studies had moderate risk of bias. These issues include: no information regarding allocation concealment (both studies), inadequate blinding of participants (Akman et al.), no clear statement of adjustment for biases (Akman et al.) and no clear statement on adjustment for various confounders. Another important limitation to these studies was the lack of power to demonstrate a difference in children with NAID. Idjradinata et al. stated: ‘If the developmental effects of non-anemic iron deficiency were smaller than those of iron-deficiency anemia then the sample size needed to detect such differences would have to be larger than the sample included in the present study’( 27 ). In addition, a comprehensive review on the effect of ID on the development of children by Grantham-McGregor and Ani (2001) specifically emphasized the importance of power and sample size( 5 ).

Relation of findings to those of similar studies

A recently published review of prophylactic administration of Fe to healthy infants and pregnant mothers showed no improvement in MDI( 30 ). Meta-analysis of three of the five included studies revealed a 4-point increase in PDI; however, the numbers of infants and studies included in the review were too small to make any conclusive recommendation for screening for ID in young children. The current review is fundamentally different from the above-mentioned one where the effect of prophylactic administration of Fe to non-ID children was examined. We focused our review on healthy children with NAID.

To date, most of the attention regarding ID has been focused on the impact of Fe treatment in children with IDA( 5 , 6 ). Studies focusing on Fe treatment for children with IDA are unable to provide relevant data for children with NAID. The reasons for this gap in knowledge include study groups not being categorized according to the different levels of ID; no control group for the subsets of ID; most studies compared IDA with Fe-sufficient children or children with lower level of ID. This underscores the importance of studies specifically aimed at children with NAID, which is a highly prevalent and under-recognized condition in young children both in developing and developed nations.

Implication on practice

Evidence is insufficient to recommend Fe treatment to children with NAID.

Implication on research

There is an urgent need for research examining the effectiveness of oral Fe treatment in children of pre-school age with NAID in respect to their developmental outcome. In order to determine if NAID is causally associated with poor development and to determine the efficacy of oral Fe treatment, adequately powered (to identify a significant difference between Fe-treated and not treated groups of children with NAID) and well-designed blinded, randomized controlled trials must be conducted. In addition, reporting of side-effects of Fe treatment should be emphasized in these trials.

Conclusions

Our findings suggest that data regarding developmental outcomes of children with NAID following treatment with oral Fe abstracted from trials specifically aimed at understanding the relationship between Fe and development in children with IDA are few and inconclusive. NAID as a cause of poor development and the efficacy of oral Fe therapy to reverse or prevent Fe-related developmental impact in this population can only be achieved by randomized trials specifically targeting children with NAID. It is imperative that these trials have adequate sample size to detect significant differences in the NAID population. Current evidence indicating the irreversible nature of IDA further strengthens the need to identify and treat children with ID while they are still in the non-anaemic stage.

Acknowledgements

Sources of funding: The Pediatric Outcomes Research Team is supported by a grant from the Hospital for Sick Children Foundation. K.A. was supported by the Ontario Graduate Scholarship (OGS, 2009) and the Canadian Institute of Health Research Masters’ Award (CIHR, 2010). Conflicts of interest: None of the authors have any conflict of interest to declare. Authors’ contributions: K.A., P.S. and P.C.P. contributed to the analysis and interpretation of data, drafting of the manuscript and critical revision of the manuscript for important intellectual content. T.K. and E.U. contributed to the search and review of articles for consideration of inclusion in the systematic review and critical revision of the manuscript. K.A. has full access to all data in the study and takes responsibility for the integrity of the data and the accuracy of the data analysis.

Appendix.

Search strategy for MEDLINE

  • 1.

    anemia, hypochromic/or anemia, iron-deficiency/or Iron/bl or exp Ferritins/bl

  • 2.

    exp Psychomotor Performance/or exp psychiatric status rating scales/or exp psychological tests/or exp child development/or mental competency/or (Bayley* adj5 scale*).ti,ab. or child behavior disorders/or exp communication disorders/or developmental disabilities/or exp learning disorders/or mental retardation/or motor skills disorders/or exp Cognition/

  • 3.

    (randomized controlled trial or controlled clinical trial).pt. or randomized controlled trials/or random allocation/or double-blind method/or single-blind method/or clinical trial.pt or exp clinical trials/or placebos/or research design/or (clinic$ adj25 trial$).mp or ((singl$ or doubl$ or trebl$ or tripl$) adj (mask$ or blind$)).mp. or (placebo$ or random$).mp. or (latin adj square).mp. or comparative study/or exp evaluation studies/or follow-up studies/or prospective studies/or cross-over studies/or (control$ or prospective$ or volunteer$).mp. or retrospective studies/or cohort studies/or cross-sectional studies/

  • 4.

    1 and 2 and 3

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