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Maternal antenatal multiple micronutrient supplementation for long-term health benefits in children: a systematic review and meta-analysis
BMC Medicinevolume 14, Article number: 90 (2016)
Multiple micronutrient supplementation for pregnant women reduces low birth weight and has been recommended in low- and middle-income countries (LMICs) to improve child survival, growth and health. We aimed to review the evidence from long-term follow-up studies of multiple micronutrient supplementation beginning in the later first or second trimester.
We searched systematically for follow-up reports from all trials in a 2015 Cochrane review of multiple micronutrient supplementation in pregnancy. The intervention comprised three or more micronutrients and the comparison group received iron (60 mg) and folic acid (400 μg), where possible. Median gestation of commencement varied from 9 to 23 weeks. Primary outcomes were offspring mortality, height, weight and head circumference, presented as unadjusted differences in means or proportions (intervention minus control). Secondary outcomes included other anthropometry, body composition, blood pressure, and cognitive and lung function.
We found 20 follow-up reports from nine trials (including 88,057 women recruited), six of which used the UNIMMAP supplement designed to provide recommended daily allowances. The age of follow-up ranged from 0 to 9 years. Data for mortality estimates were available from all trials. Meta-analysis showed no difference in mortality (risk difference –0.05 per 1000 livebirths; 95 % CI, –5.25 to 5.15). Six trials investigated anthropometry and found no difference at follow-up in weight-for-age z score (0.02; 95 % CI, –0.03 to 0.07), height-for-age z score (0.01; 95 % CI, –0.04 to 0.06), or head circumference (0.11 cm; 95 % CI, –0.03 to 0.26). No differences were seen in body composition, blood pressure, or respiratory outcomes. No consistent differences were seen in cognitive function scores.
There is currently no evidence that, compared with iron and folic acid supplementation, routine maternal antenatal multiple micronutrient supplementation improves childhood survival, growth, body composition, blood pressure, respiratory or cognitive outcomes.
Micronutrient deficiency is believed to affect approximately two billion people worldwide, with pregnant women being at particular risk because of their high metabolic demands . The World Health Organization (WHO) considers micronutrient deficiency to be of particular concern in low-income countries, where women’s diets are likely to be deficient in both quantity and quality. The importance of micronutrients is becoming increasingly apparent, especially in resource-poor settings in which women may enter pregnancy with multiple micronutrient (MMN) deficiencies [2–4]. For example, 38 % of pregnant women have iron deficiency leading to anaemia  and 15 % have vitamin A deficiency causing night blindness and increasing the risk of infection [6, 7]. Impaired antenatal nutrition can affect fetal development and growth in the short term, subsequent growth and cognitive development in the medium term, and risk of chronic disease in the longer term . There is good evidence that folic acid in pregnancy reduces neural tube defects and the mortality arising from them [8, 9]. While the evidence base is not substantial for iron and folic acid, a Cochrane review described a mean increase in birthweight of 57.7 g (95 % CI, 7.7–107.8 g) .
While there is evidence that MMN supplementation reduces the prevalence of small for gestational age (SGA) births , the primary rationale for recent recommendations to implement routine MMN supplementation for pregnant women in developing countries is that such birth weight increments will lead to reductions in childhood stunting and mortality [12, 13]. In addition to the immediate effects on health, growth in early childhood is important because of its association with adult health and human capital . The hypothesis of the developmental origins of health and disease proposes critical or sensitive periods in early development in which environmental influences can have lasting effects on growth and physiology . In humans, these critical periods are thought to occur predominantly in prenatal life and extend into early childhood. Suggested mechanisms include an interplay between environment (including maternal nutritional status), genes, and hormones, in which epigenetic regulation plays a part [3, 15, 16]. Evidence for the hypothesis comes mainly from observational studies showing associations between low birthweight and adverse adult health outcomes , from historical events such as the Dutch Hunger Winter , and from animal studies . Long-term follow-up of children born during trials of maternal MMN supplementation offer a potentially stronger test of the hypothesis. If MMN supplements are to be recommended for pregnant women, it is important to know whether they lead to the sustained improvements in child health predicted by an increase in birthweight. In this review, we searched for reports that followed up the trials included in the 2015 Cochrane review , focusing on childhood mortality and health-related outcomes (growth, body composition, cardio-metabolic risk markers, cognition, lung function). We hypothesized that, compared with iron and folic acid, antenatal MMN supplementation would lead to longer-term improvements in health and survival.
Types of report
We attempted to find all reports of follow-up of children born in the individual or cluster randomized controlled trials included in the 2015 Cochrane review. The review included 17 trials and excluded 97. The main reasons for exclusion were not meeting intervention and comparison group criteria, not assessing supplementation in a healthy population, and providing supplementation within food fortification initiatives .
Participants were children born in the trials in the 2015 Cochrane review  who had been subsequently followed up.
Intervention and comparison groups
The intervention group included women who had received multiple micronutrient supplements, defined as “containing three or more micronutrients” in pregnancy . All intervention groups received iron and folic acid. For consistency, the comparison group chosen a priori was iron 60 mg and folic acid 400 μg, where possible, as this regimen is generally recommended for pregnant women . We planned to consider all trials together, with the possibility of subgroup examination when supplementation regimens differed. Trials with co-interventions (for example, food supplements) were eligible provided that the co-intervention was similar in both allocation arms. If a second randomization was conducted after birth, we did not include arms that received MMN supplements in the comparison group.
The primary outcomes were mortality (difference per 1000 livebirths), height and weight (as continuous WHO z scores, adjusted for age and sex), and head circumference (continuous difference), presented as unadjusted differences (intervention minus control). At a population level, risk differences may be more interpretable than odds ratios because they give a clearer impression of the effects of an intervention in terms of potential policy. When not reported, we calculated mean differences with 95 % confidence intervals. Mortality difference was either as described in the trial paper or follow-up report, or calculated from available trial profiles. Secondary outcomes included categorical proportions of stunting (< –2 z scores height-for-age), underweight (< –2 z scores weight-for-age), wasting (< –2 z scores weight-for-height) and low body mass index (BMI) (< –2 z scores BMI-for-age), descriptions of body composition (lean and fat mass, skinfold thickness), blood pressure, cognitive tests, and lung function. Cognitive and motor development were as assessed by trialists, including use of indexes such as the Bayley Mental Development Index, Bayley Psychomotor Development Index, Stanford-Binet Test, DENVER II Developmental Screening Test and Wechsler Intelligence Scale for Children. Effect modification by maternal nutritional status and child sex was reported when available. Birth outcomes were not considered as they had been reported previously [11, 22].
Search strategy and study selection
We searched PubMed, Web of Science and the Global Health Library for articles that included trial lead author names, location, trial number, or the given trial name (Additional file 1: Text S1). We contacted trial authors when eligibility was unclear and used a snowballing approach, searching citation lists and ‘related articles’. Study titles and abstracts were screened for eligibility by DD and JCKW independently. Differences were resolved by discussion. Full papers were obtained for potentially eligible citations. The results were assessed for multiple publications and one study was excluded. We did not assess reports of maternal outcomes. No exclusions were applied for age, dates of coverage, or language.
Data extraction and analysis
Publications from each trial were examined by two review authors (unconnected with the trial) independently (AC, BM, CHDF, DD, DO, HSS, and JCKW), using a pre-tested data extraction form. Differences were resolved by discussion. We contacted trial authors for clarifications and consolidated multiple reports from the same trial using data from the later follow-up. We used anthropometric z scores adjusted for age and sex (WHO reference ranges). Meta-analyses were conducted if sufficient reports were available, using the DerSimonian and Laird model. When numbers of deaths were provided for a sub-group of participants in a second age interval, we combined the data to produce an estimate of the mortality rate across both intervals using standard life-table techniques, and generated 95 % confidence intervals through a simulation approach. Outcome measures were risk differences per 1000 livebirths (mortality), differences in anthropometry z scores (height-for-age (HAZ) and weight-for-age (WAZ)) and absolute values (head circumference and blood pressure). We assessed heterogeneity using the I2 statistic. In view of anticipated contextual heterogeneity, we used a random effects model for all meta-analyses. Missing data were reported under attrition bias, but no further analyses were conducted. For cluster-randomised trials, we used reported cluster-adjusted estimates, irrespective of the method employed. If the analyses had not been adjusted for cluster design effect, we used a previously reported design effect from the trial paper to inflate the variance. Analysis was conducted in Stata, version 12 (StataCorp, College Station, TX, USA).
Risk of bias
Risk of bias for each study was assessed by two review authors (unconnected with the trial) independently (AC, BM, CHDF, DD, DO, HSS, and JCKW), using a pre-tested data extraction form. Differences were resolved by discussion and trial authors were contacted for clarifications. We used the same categorisation of bias of individual trials as in the Cochrane review 2015. We reported on bias in follow-up reports in the following categories: selection, attrition, reporting, performance and detection. We evaluated reporting bias by inspection of funnel plots for the primary outcomes of mortality, weight-for-age, height-for-age and head circumference.
We performed sub-group analyses including trials that used UNIMMAP only and trials with different iron dosage (~30 or 60 mg) in control groups. Sensitivity analyses were not conducted.
Description of trials with follow-up reports
Follow-up reports were identified for nine of the trials in the Cochrane review. In total, 88,057 women were recruited. The trials were spread geographically: two in Africa [23, 24], one in the Americas , and six in Asia [26–31]. All sites were rural, with the exception of Nepal Janakpur (urban and rural) and Guinea (semi-urban). Mean ages of mothers were similar and ranged from 21.5 (Nepal Janakpur) to 25.6 years (Indonesia). Mean maternal BMI, measured at recruitment during pregnancy, ranged from 19.3 kg/m2 (Nepal Sarlahi) to 24.1 kg/m2 (Mexico). Trial characteristics, with results summarized in the way in which they were presented in the trial papers, are shown in Table 1 and have been previously described in detail [20, 32].
Six of the nine trials used the UNIMMAP supplement developed by UNICEF, the United Nations University, and WHO, and were designed to provide the recommended daily allowances. It contained vitamin A 800 μg, thiamine 1.4 mg, riboflavin 1.4 mg, niacin 18 mg, vitamin B6 1.9 mg, folic acid 400 μg, vitamin B12 2.6 μg, vitamin C 70 mg, vitamin D 5 μg, vitamin E 10 mg, copper 2 mg, iodine 150 μg, iron 30 mg, selenium 65 μg, and zinc 15 mg . The Bangladesh JiVitA trial used the same micronutrients as UNIMMAP in similar doses. The supplement used in Nepal Sarlahi contained micronutrients in similar doses (with 60 mg iron), plus magnesium and vitamin K, but no selenium or iodine . The supplement used in Mexico included iron 62.4 mg and magnesium 252 mg, and did not include copper, iodine or selenium . In some cases, a comparison group of iron 60 mg and folic acid 400 μg was not available: Nepal Sarlahi included additional vitamin A , Mexico did not include folic acid , Indonesia used 30 mg iron , and Bangladesh JiVitA used 27 mg iron and 600 μg folate . Supplement constituents are shown in Additional file 1: Table S1. Supplementation was initiated in early to mid-pregnancy, with a range of median commencement gestation across studies of 14 weeks (Table 1).
We found 20 follow-up reports (Table 2 and Additional file 1: Figure S1). We divided the findings into five general categories: mortality [26, 27, 35–41], anthropometry [35, 38, 39, 41–44] and body composition [39, 44, 45], cardiovascular [39, 43, 46, 47], cognitive [37, 48–51], and respiratory . Primary publications from the Bangladesh JiVitA and MINIMat trials included follow-up mortality data and were included in the list of follow-up reports. Meta-analyses were conducted for mortality, weight, height, head circumference and blood pressure outcomes.
Follow-up reports from all trials systematically recorded and reported infant/child mortality as an outcome (Table 3). Meta-analysis showed no difference between intervention and control groups (risk difference, –0.05 per 1000 livebirths; 95 % CI, –5.25 to 5.15; I2, 8 %; Fig. 1). No difference by age was seen. Subgroup analysis including trials that used only the UNIMMAP supplement showed a risk difference of 3.41 per 1000 livebirths (95 % CI, –4.45 to 11.26; I2, 0 %; Additional file 1: Figure S2). Subgroup analysis for trials that used 60 mg iron in control groups yielded a risk difference of 4.51 per 1000 livebirths (95 % CI, –2.91 to 11.94; I2, 0 %), and trials that used approximately 30 mg iron in the control group yielded a risk difference of 0.41 per 1000 livebirths (95 % CI, –14.76 to 15.57; I2, 62 %; Additional file 1: Figure S3).
Seven reports described anthropometry (Table 4). No differences were seen in any report at the most recent follow-up for WAZ, HAZ or head circumference, nor in any secondary anthropometric outcomes. Differences were seen at younger ages in two trials. In the Burkina Faso trial, greater mean WAZ (β, 0.13; 95 % CI, 0.04 to 0.23) and length-for-age z score (β, 0.13; 95 % CI, 0.02 to 0.24) were seen in the multiple micronutrient supplement group, and a lower proportion were stunted at 1 year (hazard ratio, 0.73; 95 % CI, 0.60 to 0.87), but there was no difference at 2.5 years of age . In the Nepal Janakpur trial, greater mean WAZ (β, 0.14; 95 % CI, 0.00 to 0.27) was seen in the multiple micronutrient supplement group at a mean of 2.5 years, but there was no difference at 8.5 years (β, 0.05; 95 % CI, –0.09 to 0.19). Small increases were seen in head, chest, hip, and mid-upper arm circumferences at 2.5 years, but were also not present at 8.5 years [39, 43].
Effect modification by maternal BMI or child sex was not found in any report with the exception of the Bangladesh MINIMat trial, in which stunting was greater in boys in the MMN group (Males, 7.8 %; 95 % CI, 2.0 to 13.6; Females, 1.8 %; 95 % CI, –3.8 to 7.3). A test for interaction was not reported.
Meta-analyses for WAZ and HAZ showed no difference between multiple micronutrient and 60 mg iron and folic acid groups. The differences in WAZ and HAZ were 0.02 (95 % CI, –0.03 to 0.07; I2, 0 %; Fig. 2) and 0.01 (95 % CI, –0.04 to 0.06; I2, 0 %; Fig. 3), respectively. Meta-analysis for head circumference was possible for three trials (Mexico, Bangladesh MINIMat and Nepal Janakpur) and showed no difference (0.11 cm; 95 % CI, –0.03 to 0.26; I2, 0 %; Fig. 4). Subgroup analysis including UNIMMAP trials made little difference: WAZ 0.04 (95 % CI, –0.01 to 0.09; I2, 0 %), HAZ 0.01 (95 % CI, –0.05 to 0.06; I2, 0 %), and head circumference 0.11 cm (95 % CI, –0.05 to 0.26; I2, 10 %; Additional file 1: Figure S2).
The Bangladesh MINIMat trial found no difference in biceps, triceps, subscapular or suprailiac skinfold thicknesses. The Nepal Janakpur trial found an increase in triceps skinfold thickness at 2.5 years (0.20 mm; 95 % CI, 0.00 to 0.40 mm) , but no difference was found in any skinfold thickness at 8.5 years . The Nepal Sarlahi trial found no difference in triceps or subscapular skinfold thickness at 7.5 years of age. Neither the Bangladesh MINIMat nor the Nepal Janakpur trial found a difference in lean mass or fat mass measured using bio-impedance [39, 45, 53, 54].
Cardiovascular risk markers
Cardiovascular outcomes were only examined in trials from South Asia (Table 4). The Bangladesh MINIMat and Nepal Janakpur trials measured blood pressure, while the Nepal Sarlahi trial investigated metabolic syndrome (blood pressure, HbA1c, urine microalbumin:creatinine, cholesterol, glucose, insulin, homeostasis model assessment of insulin resistance). The Nepal Janakpur cohort showed a reduction in mean systolic blood pressure of 2.5 mmHg (95 % CI, 0.47 to 4.55) at 2.5 years of age, but no difference at 8.5 years (0.02 mmHg; –1.02 to 1.05) [39, 43]. The Bangladesh MINIMat cohort showed no difference at 4.5 years compared with a control group who received iron 30 mg and folic acid . The Nepal Sarlahi trial found neither a difference in blood pressure at 7.5 years, nor a difference in other cardiovascular risk markers compared with a control group who received iron 60 mg and folic acid . Meta-analysis of the three trials showed no difference in blood pressure: the difference in systolic blood pressure was 0.11 mmHg (95 % CI, –0.41 to 0.63; I2, 0 %), and in diastolic pressure 0.47 mmHg (95 % CI, –0.01 to 0.95; I2, 0 %; Additional file 1: Figure S4). Subgroup analysis for trials that used iron 60 mg in the control group was similar: systolic blood pressure difference 0.16 mmHg (95 % CI, –0.54 to 0.87; I2, 0 %), and diastolic 0.37 mmHg (95 % CI, –0.35 to 1.08; I2, 0 %; Additional file 1: Figure S3).
The Bangladesh MINIMat, China, and Indonesia trials all assessed subgroups of children: in Bangladesh, children born in a 19-month period, at 7 months of age ; in China, in the middle year of the trial up to 1 year of age  and at 8.8 years ; and in Indonesia, in women assigned to blood tests and whose children were born in a 6-month time period, at 3.5 years of age . The Nepal Sarlahi study administered cognitive, motor and executive function tests at 7–9 years of age. Mean cognitive scores were a little lower for the MMN group compared to iron, folic acid and vitamin A (Universal Nonverbal Intelligence Test score, –2.4; 95 % CI, –4.6 to –0.2). Results of motor and executive function tests were mixed . The Bangladesh MINIMat and China trials found no difference in motor or psychomotor scores [48, 49]. The Indonesia trial found an increase in motor ability in an adjusted analysis expressed as a fraction of the variation of the score (0.19; 95 % CI, 0.02 to 0.37) . The Bangladesh MINIMat follow-up found no difference in problem solving or behaviour . In the China trial, there were no differences at 3 or 6 months, but age-adjusted scores at 1 year were higher for mental development in the MMN supplementation group (1.20 points; 95 % CI, 0.32 to 2.08: equivalent to about 6 days of age) . At 8.8 years of age, there were no differences in cognitive scores compared to folic acid or to iron and folic acid groups . The Indonesia trial follow-up found no difference in visuospatial and visual attention, executive functioning, language ability, or socioemotional development .
For completeness, we mention stratified analyses. In the Bangladesh MINIMat trial, stratification by maternal BMI, combining the early and usual food groups together, showed an increase in Psychomotor Development Index in children whose mothers had been allocated to MMN supplements and had BMI < 18.5 kg/m2 (0.22 z scores; 0.01 to 0.42; interaction term, P = 0.05) . In Indonesia, MMN supplementation was associated with greater motor ability (β = 0.35 z scores; 95 % CI, 0.01 to 0.69, interaction term, P = 0.04) and visual attention/spatial ability (β = 0.35; 95 % CI, 0.08 to 0.63, interaction term, P = 0.01) in children of undernourished mothers (MUAC, < 23.5 cm). These differences were equivalent to approximately 5 months of age .
The Nepal Janakpur trial investigated lung function at 8.5 years of age. Spirometry data were obtained from 836 children, with 793 (95 %) achieving optimal results using American Thoracic Society/European Respiratory Society guidelines . No difference in lung function was found between allocation groups: forced expiratory volume in the first second, –0.01 L (95 % CI, –0.04 to 0.02 L); forced vital capacity, –0.01 L (95 % CI, –0.04 to 0.02 L) .
Assessment of bias
The trials were considered high quality and bias was not thought to be important. There was potential selection bias in the Guinea-Bissau trial as a result of inadequately concealed allocation , and potential attrition bias for the Nepal Janakpur and Mexico trials, in which exclusions prior to randomization were not reported [25, 30].
The trials were powered on the primary outcomes of gestational age and birthweight (and mortality, in the case of the Bangladesh JiVitA Indonesia trials) . Follow-up reports described power or sample size calculations before data collection, with the exception of the Bangladesh MINIMat (cardiovascular) , Burkina Faso (anthropometry)  and Nepal Sarlahi (anthropometry and cardiovascular reports) follow-up publications [44, 47]. There was little statistical heterogeneity, with I2 values low for primary analyses (0–8 %). Some clinical heterogeneity was present as participants were from different countries and ages of follow-up varied. The intervention was the same in most cases, but (as described above) the Bangladesh JiVitA, Mexico and Nepal Sarlahi trials used slightly different multiple micronutrient formulations, and the Bangladesh JiVitA, Indonesia, Mexico and Nepal Sarlahi trials used different controls. Although choice of outcomes varied from one report to another, similar methods were used to assess similar outcomes.
Primarily a result of inadequate randomisation and allocation concealment, this has been covered in the 2015 Cochrane assessment . An additional potential source of bias is selection of trials from the Cochrane review that did not show an increase in birthweight associated with MMN supplementation. The Cochrane review included 14 trials in its analysis of SGA. Of the five not considered here [56–60], one showed a significant reduction in SGA (Fawzi et al. , Tanzania; RR, 0.79; 95 % CI, 0.70–0.89). Supplement composition was substantially different in this trial, which compared a supplement containing eight vitamins and no minerals with a 60 mg iron and 250 μg folic acid control . Meta-analysis of the trials included in our review showed an increase in birthweight of 30.2 g (95 % CI, 14.1 to 46.3), which is similar in magnitude to that found in previous meta-analyses [11, 61–63]. Similarly, three of the 11 trials included in the meta-analysis of neonatal mortality did not conduct follow-up studies. None of these trials showed a reduction in neonatal mortality. Meta-analysis of neonatal mortality rate for included trials produced an RR of 1.01 (95 % CI, 0.90 to 1.16).
Performance and detection bias
Participants and data collectors in all follow-up reports remained blind to allocation, with the exception of Guinea-Bissau, where this was not mentioned explicitly in the report.
While all reports described loss to follow-up (Table 2), attrition bias was relatively small (0–29 %), except in the Mexico trial, in which just over half the children were seen at 24 months. The largest group lost were too old (>3 months) at the start of the follow-up. Excluding this group, follow-up rates were similar to those of the other reports. No important differences in loss to follow-up between allocation groups were reported, with the exception of China at 9 years, where study groups differed by school type, recent respiratory tract infection, mother’s occupation (farmer or other) and father’s level of education. These biases work in opposite directions and were accounted for in the analyses . Where recorded, differences between children retained and lost to follow-up were small. Children lost to follow-up tended to have mothers with more education (Bangladesh MINIMat, Nepal Janakpur, Mexico and Nepal Sarlahi), lower parity and younger age (Bangladesh MINIMat and Mexico), and were more likely to live in an urban location (Nepal Janakpur), have differences in ethnicity and assets (Nepal Sarlahi), and lower birthweight and shorter gestation (Bangladesh MINIMat). Maternal age, weight, height and parity also differed in Guinea-Bissau, but the directions of these effects were not reported. Although most reports did not enumerate them, losses for individual outcomes also occurred: (>20 % loss to measurement) kidney volume and function in the Bangladesh MINIMat trial, body composition in the Nepal Janakpur trial, and fasting glucose, insulin and homeostasis model assessment in the Nepal Sarlahi trial.
We could not make a definitive assessment of reporting bias as follow-up protocols were unpublished, but funnel plots for mortality, HAZ, WAZ and head circumference, using results from the most recent follow-up report, did not suggest publication bias for the primary outcomes (Additional file 1: Figure S5).
We found 20 follow-up reports for nine trials, covering a range of health outcomes. Nine studies reported on mortality, six on weight, six on height, and four on cognitive function, but there were few reports of other outcomes. Our hypothesis was not confirmed – we found no evidence that antenatal MMN supplementation, compared with iron and folic acid supplementation, led to improved survival, improved growth, lower blood pressure, or improved lung function in childhood. Potential improvements in cognitive outcomes were observed, but these were small and inconsistent and tended to be seen in subgroups.
Quality of trials and limitations of the review
The trials had low risks of bias and were generally considered of high-quality . The degree of loss to follow-up was not substantial, although in some cases only subgroups were followed up. Differential loss to follow-up between intervention and control groups did not appear to be an issue, and neither did selective publication, as most trials reported null findings. The evidence on antenatal MMN supplementation comes from a large sample and a substantial number of trials, many of which were coordinated. The trials considered here were spread geographically, although 13 of the 20 follow-up reports were from South Asia, which may have affected generalizability. Differences between the Nepal and Bangladesh reports emphasize the fact that variation can occur within similar populations.
The main limitation was that not all trials had published reports on follow-up. We cannot be certain whether a selection bias exists, but we found no indication of this. Follow-up reports have published null findings, rather than positive ones. If a publication bias does exist, it would not work in this direction. None of the trials had initially set out to observe childhood outcomes. While power calculations were performed prior to most follow-ups, trials were powered on birth outcomes and larger sample sizes may be required to detect small differences in childhood. Functional outcomes were measured at different ages and may not be comparable. We attempted to address this by using z scores, adjusted for age and sex, as primary outcomes. This was not always possible and limits inferences from the head circumference and blood pressure findings. We tried to make comparisons as similar as possible, but our findings could be vitiated by slightly different MMN and control supplement compositions in some trials.
Antenatal MMN supplementation was initially hypothesized to reduce mortality, but increases in neonatal mortality were suspected in some trials . A meta-analysis did not find a difference in neonatal mortality overall, but raised concerns about increased early neonatal mortality (OR, 1.23; 95 % CI, 0.95 to 1.59). The 2015 Cochrane review found a reduction in stillbirths (0.91; 95 % CI, 0.85 to 0.98, n = 15), and no effect on perinatal (0.97; 95 % CI, 0.84 to 1.12, n = 12) or neonatal mortality (0.98; 95 % CI, 0.90 to 1.07, n = 11) . The reduction in stillbirths is interesting and potentially important . It depended on the analytical weighting (57 %) of the study by West et al.  and the use of a fixed effects model, and requires confirmation. A suggestion that MMN supplementation would prevent 43,715 annual child deaths (with 90 % coverage in 34 countries most in need) followed from the Lives Saved Tool model, based on evidence that reductions in the prevalence of SGA are associated with reduced stunting and subsequent child survival . Our analyses did not identify evidence of an effect on child mortality and do not support the assumptions made in the Lives Saved Tool.
Anthropometry and body composition
Overall, follow-up reports did not show differences in anthropometry or body composition. A transient improvement was seen in early life in the Burkina Faso and Nepal Janakpur trials, and there was a suggestion of increased stunting in Bangladesh, but these findings were not replicated in other reports. There was a consistent lack of effect on height. It is conceivable that MMN supplementation could have physiological effects that are not manifest in substantial anthropometric change. For example, transient greater weight in early childhood could have long-term benefits, even if not apparent in the short-term.
Small improvements in mental development were seen in China  at 1 year but not at 9 years, cognitive score was lower in Nepal Sarlahi , and the Bangladesh MINIMat and Indonesia trials found improvements in subgroups of mothers with poorer nutritional status only [37, 48]. Considering the number and range of tests conducted, antenatal MMN supplements did not appear to lead to a consistent cognitive benefit. When found, differences tended to be small and three of the five reports involved children under 4 years, in whom cognitive tests are less reliable than in older children. Further assessment of these cohorts is warranted.
Comparison of follow-ups did not confirm the impression of transiently lower systolic blood pressure at 2.5 years in the Nepal Janakpur trial, or of improved lung function in children seen in a similar trial of vitamin A supplementation from Nepal Sarlahi . Only one trial considered other cardiovascular risk markers and found no effects.
On the basis of the reports we have reviewed, current evidence does not support changing the recommendation for routine antenatal supplementation from iron and folic acid to MMN formulations. It is possible – even probable – that the trial populations differed in their patterns of micronutrient deficiency. There was little evidence to suggest that this influenced the general findings. Although there is consistent evidence that antenatal MMN supplementation increases birth weight, none of the studies demonstrated convincingly that it benefitted offspring in terms of functional or health outcomes, and the directions and magnitudes of effect were similar for mortality and anthropometric outcomes across the study sites. The findings of the Cochrane review on which recent advocacy for routine antenatal MMN supplementation are based are supported by other meta-analyses that have shown an increase in mean birthweight of 22–54 g and corresponding reductions in low birthweight and SGA. As may be expected, the erosion over time of anthropometric differences observed at birth suggests that infants of women who received antenatal MMN supplements lost an advantage over the first few years. This could be the result of numerous environmental stresses over postnatal life. No other changes in anthropometry, gestation or mortality were found [11, 20, 22, 61–63]. However, improvement in later health outcomes does not necessarily depend on supplementation causing an increase in birthweight (or organ size). The mechanisms of action are likely to be multifactorial and follow-up reports suggest other mechanisms such as the effect of vitamin A on regulation of fetal lung growth, branching and alveolarisation [67, 68]. We also cannot rule out effects emerging later in life or in the next generation. From an evolutionary perspective, supplementing mothers could potentially benefit the woman herself, the index baby, or future offspring. Antenatal micronutrient supplementation has a role in women with a deficiency-related illness, and possibly in micronutrient deficiency itself, but population supplementation may need to start earlier, either in the first trimester or pre-conception, to include the period of rapid organogenesis and genome-wide epigenetic changes that follow fertilization, and be continued into childhood [16, 69, 70]. The formulations of MMN tested may also not be the optimum ones. We cannot rule out the possibility that combinations other than the ones tested might have positive outcomes. It is possible that additional micronutrients, or different doses, might result in functional benefits.
The annual cost of MMN supplementation in pregnancy (at 90 % coverage) in the 34 LMICs in which it would be most useful is estimated at (International)$ 472 million . If, as our review suggests, initiating antenatal MMN supplementation in early/mid-pregnancy does not lead to the anticipated improvements in childhood function or health – the main current justification for recommending it – the opportunity costs to other programmes that do lead to improvements will need to be considered.
Implications for future research
More evidence is needed, especially on cognitive development, cardiovascular risk markers and lung function, to adequately appraise the long-term effects of antenatal MMN supplementation. We recommend follow-up studies in more of the MMN trials. Further research into biological mechanisms by which an early advantage could be attenuated will help in our understanding of the intervention and in designing future trials.
In summary, our review of published follow-up reports has not shown persisting effects of antenatal MMN supplementation during childhood, compared with iron and folic acid. Phenotypic and physiological differences may arise later in life or as more research is conducted, but the current evidence base is insufficient to support routine MMN supplementation in pregnancy at a population level in low- and middle-income countries.
BMI, body mass index; HAZ, height-for-age z score; MMN, multiple micronutrient; SGA, small for gestational age; WAZ, weight-for-age z score; WHO, World Health Organization.
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Heather Chesters helped perform the literature search.
There was no specific funding for this study. DD is supported by the National Institute of Health Research. DO is supported by The Wellcome Trust (091561/Z/10/Z). HSS receives support from Sitaram Bhartia Institute of Science and Research, New Delhi. CHDF and CO are supported by the Medical Research Council and Department for International Development.
DD and JCKW performed the literature search. AC, BM, CHDF, DD, DO, HSS, and JCKW reviewed the reports and extracted the data. DD and CO performed the analysis. DD wrote the first draft. All authors read and criticised drafts of the manuscript.
The authors declare that they have no competing interests.
Consent for publication
There is no individual person data.
Ethics approval and consent to participate
Not applicable. The paper is a review of published research and there was no primary data collection.
The search strategy, micronutrient constituents, PRISMA flow chart, sub-group analyses and funnel plots. (PDF 305 kb)