The critical nature of pregnancy, infancy and early childhood for lifelong development is echoed across multiple disciplines. A child’s health and development is shaped by his/her genes and a range of intrinsically connected environmental factors including socio-economic status (SES) and parenting practices( Reference Bradley and Corwyn 1 ). Nutrition also influences a child’s development, with effects beginning prior to birth and continuing into adulthood( Reference Haschke, Haiden and Detzel 2 ). Such individual environmental factors are complicated by the connections between them. For example, parenting and food-related parenting practices may influence children’s eating behaviour, dietary intake and food preferences( Reference Sleddens, Kremers and Stafleu 3 ). In addition, SES indicators are associated with general parenting( Reference Ermisch 4 ) and food-specific parenting practices( Reference Loth, MacLehose and Fulkerson 5 ), while positive parenting can mediate the negative impact of low SES on cognitive outcomes( Reference Kelly, Sacker and Del Bono 6 ). Thus, identifying targeted interventions which alter the food-related parenting practices of low-SES families is a salient issue.
Diet supplies the nutritional substrates required for rapid growth and brain development. Key nutrients include protein, iron, zinc, selenium, iodine, folate, vitamin A, choline and long-chain PUFA( Reference Georgieff 7 ). Evidence from developing countries shows that undernutrition in early childhood is associated with poorer cognitive development and academic performance( Reference Grantham-McGregor, Cheung and Cueto 8 ). In developed countries, breast-feeding has been associated with improved cognitive development in observational studies( Reference Anderson, Johnstone and Remley 9 ). The majority of research examining the relationship between diet and cognition focuses on individual nutrients( Reference Nyaradi, Li and Hickling 10 ); however, some studies have examined food groups, such as animal-source foods, and reported significant positive associations with cognitive functioning( Reference Kramer, Aboud and Mironova 11 ).
A limited number of studies have examined the association between whole dietary intake and cognitive development based on dietary pattern analysis( Reference Northstone, Joinson and Emmett 12 , Reference Smithers, Golley and Mittinty 13 ) or a score/index system representing adherence to dietary guidelines( Reference Nyaradi, Li and Hickling 14 ). Reports from the Avon Longitudinal Study of Parents and Children suggest that ‘discretionary’ or ‘processed’ dietary patterns in infancy and early childhood are negatively associated with intelligence quotient (IQ), while ‘breast-feeding’ and ‘homemade contemporary’ patterns are associated with a higher IQ( Reference Northstone, Joinson and Emmett 12 , Reference Smithers, Golley and Mittinty 13 ). The Western Australian Pregnancy Cohort Study also reported a significant positive correlation between diet at age 1 year and cognitive outcomes at age 10 years by consolidating dietary intake to generate a single diet score( Reference Nyaradi, Li and Hickling 14 ). These studies found that adjusting for covariates, including SES, attenuated the relationship between diet and IQ; however, the associations remained statistically significant.
Given the links between SES and diet( Reference Smithers, Brazionis and Golley 15 ), different types of nutrition interventions targeting disadvantaged children have evolved( Reference Williams, Cates and Blitstein 16 – 18 ). Multifaceted interventions, such as home visiting programmes (HVP), have a broader remit than nutrition-focused interventions and typically target the holistic development of the child through improving parenting practices. By aiming to improve the child’s development, HVP may also impact upon dietary practices. Systematic reviews of HVP have identified effects on parenting practices, child health and cognitive development( Reference Avellar and Supplee 19 , Reference Peacock, Konrad and Watson 20 ). Yet few HVP have measured children’s dietary practices. Exceptions include two HVP reporting a positive impact on breast-feeding practices( Reference Johnson, Howell and Molloy 21 , Reference Kitzman, Olds and Henderson 22 ) and others reporting effects on fruit and vegetable consumption and overall dietary intake( Reference Johnston, Huebner and Anderson 23 – Reference Wen, Baur and Simpson 25 ).
The present study is a randomised controlled trial examining the impact of the Preparing for Life (PFL) HVP on maternal reports of adherence to food-based dietary guidelines from 12 to 36 months of age and the mediating role of diet on cognitive functioning. PFL is a 5-year programme that aims to improve children’s health and development in disadvantaged communities. The ultimate goal of the programme is to improve children’s school readiness skills at age 4/5 years by intervening during pregnancy and working with families until the children start school. The programme adopts a holistic view of school readiness in accordance with best practice which identifies five domains of importance: (i) physical health and well-being; (ii) socio-emotional development; (iii) approaches to learning; (iv) language development and emergent literacy; and (v) cognition. The present study examines the evolving impact of the programme on two of these domains: physical health and cognition.
Methods
The trial was registered with controlled-trials.com (ISRCTN04631728, http://www.controlled-trials.com/ISRCTN04631728/) and was conducted and reported in conformity with CONSORT (Consolidated Standards of Reporting Trials) guidelines.
Participants
The study design and protocol have been described elsewhere and are summarized below( 26 ). The PFL programme enrolled pregnant women from a community in Dublin, Republic of Ireland, which had above national average rates of unemployment (16 % v. 5·3 %), school dropout (66 % v. 38 %), lone-parent households (47 % v. 29 %) and public housing (60 % v. 20 %) prior to recruitment. The inclusion criteria included all pregnant women living in the catchment area, regardless of parity. There were no exclusion criteria. Participation was voluntary and recruitment took place through two maternity hospitals or self-referral in the community by the PFL recruitment officer between 2008 and 2010. Written informed consent was obtained from all participants prior to randomisation. The sample size was calculated based on small to moderate effect sizes (standardised difference between group means) on the primary outcomes of child school readiness as identified by previous meta-analytic studies( Reference Sweet and Appelbaum 27 ) with a power of 80 % (P=0·05, two-tailed test).
An unconditional probability randomisation procedure assigned 115 participants to the intervention group and 118 to the control group. No stratification or block techniques were used. To ensure randomisation was not compromised each participant clicked on the randomisation website where she was automatically assigned a number which corresponded to her treatment assignment. This process generated an automatic email with her assignment condition and identification code, thus ensuring that participants could not be reassigned once randomised.
Intervention
Participants were assigned to an intervention group receiving a community-based HVP and an additional parenting course, or to a control group. HVP provide parents with information, instruction on parenting practices, emotional support and access to community services( Reference Howard and Brooks-Gunn 28 ). PFL prescribed twice monthly home visits, lasting approximately an hour, delivered by mentors with college degrees in education, social care and youth studies. The aim of the visits was to support and educate the parents on the identification of developmental milestones and appropriate parenting practices that promote children’s health and development. Between programme entry and age 3 years the average number of visits delivered was fifty-one, which was below the eighty-eight home visits prescribed during this period (58 %). Mentors received extensive training prior to programme implementation and monthly supervision thereafter. Each family was assigned the same mentor over the course of the intervention where possible. The mentors used role modelling, demonstration, coaching, discussion, encouragement and feedback to deliver the intervention. Visits were guided by Tip Sheets which were tailored based on the age of the child and the needs of the family. Forty-six Tip Sheets delivered between programme entry and age 3 years emphasised child nutrition and dietary recommendations and included topics such as ‘breast-feeding’, ‘iron and calcium’, ‘the food pyramid’ and ‘food groups’. For example, a Tip Sheet on iron stated that ‘Iron is a very important part of your child’s diet as it helps both physical and mental development. Even a short-term lack of iron could cause your child to become iron deficient and anaemic.’ The ‘food pyramid’ and ‘food group’ Tip Sheets provided information on dietary recommendations including examples of portions of foods within groups. An example of this Tip Sheet is provided in the online supplementary material.
The intervention also included the delivery of the Triple P Positive Parenting Program( Reference Sanders, Kirby and Tellegen 29 ) between 2 and 3 years of age. Triple P promotes healthy parenting practices and positive parent–child attachment, and meta-analysis has demonstrated positive effects regarding parenting practices and children’s social, emotional and behavioural outcomes( Reference Sanders, Markie-Dadds and Turner 30 ). Sixty-two per cent of intervention participants who completed the interview at age 3 years took part in some form of Triple P, with the majority availing of Group Triple P which consists of five 2 h group discussion sessions and three individual telephone calls facilitated by the mentors. The group-based sessions, including about eight to ten parents in each group, aimed to improve positive parenting through the use of role play, videos, vignettes and Tip Sheets.
The intervention and control groups received some common supports including child developmental materials and book packs, and were encouraged to attend public health workshops on stress management and healthy eating. Only eighteen mothers in the intervention group and nine mothers in the control group participated in the healthy eating workshops. They also had access to a support worker who could help them avail of community services if needed. Note that the control group did not receive the HVP, Tip Sheets or Triple P.
Data collection and measures
All interviews were conducted by trained interviewers who were blinded to participants’ treatment status and not involved in intervention delivery or data analysis. Each participant received a €20 shopping voucher per interview.
Dietary intake
Food frequency questions were adapted from the Lifeways Cross-Generation Cohort Study( Reference Shrivastava, Murrin and Sweeney 31 ) by combining fifty-two individual food items into the six main food groups reflecting national healthy eating guidelines and the food pyramid groups. At the 12-, 18-, 24- and 36-month interviews, mothers were asked how often their child ate grains (i.e. cereals, breads, potatoes, pasta and rice food group), dairy (i.e. milk, yoghurt and cheese food group), protein (i.e. meat, poultry, fish and alternatives food group), fruit (including juices), vegetables (including juices) and other foods (including sugars and fats, sweets, crisps, etc.) on a 9-point scale ranging from ‘never’ to ‘more than 6 times per day’. Six binary variables were created indicating whether the child consumed the recommended daily number of servings as set out in the Food and Nutrition Guidelines for Pre-school Services ( 32 ) and as endorsed by the PFL Tip Sheets. Hereafter, ‘grains’, ‘protein’ and ‘dairy’ refer to their respective food groups. Participants who stated that their child consumed two to three servings or more of grains, protein and dairy daily were coded as meeting recommendations. Children who consumed four or more total portions of fruit and vegetables daily were classified as meeting recommendations. For ‘other foods’, children who consumed fatty/sugary foods less than once daily were coded as meeting recommendations. The final binary variable indicated whether the participant met all four dietary recommendations for each food group excluding ‘other foods’.
Developmental Profile-3: cognitive section
Cognitive development was assessed at 24 and 36 months using the thirty-eight-item parent report Developmental Profile-3: cognitive section (DP-3)( Reference Alpern 33 ). Each item referred to tasks which required cognitive skill; for example, ‘Does your child point to at least twenty things or pictures when they are named?’ For each item, mothers were asked whether their child had carried out the task. The ‘yes’ responses were tabulated to create a continuous score, whereby higher values indicated greater cognition. Scores were standardised to have a mean of 100 and an sd of 15 (24 months, α=0·80; 36 months, α=0·77).
Statistical analysis
All intention-to-treat analyses were pre-specified and conducted using the statistical software package STATA MP 12. Conventional χ 2 tests from logistic regressions were used to assess differences between the intervention and control groups. In addition, to test the robustness of these results, permutation-based hypothesis tests were used. Permutation testing does not depend on distributional assumptions and thus is more appropriate in small samples( Reference Ludbrook and Dudley 34 ). Simulation studies have found that permutation testing has superior power advantages over conventional tests, particularly if the outcome data are skewed and the degree of skewness is correlated with the size of the treatment effect( Reference Keller 35 ). In addition, to reduce the probability of Type I errors, which may arise when analysing multiple outcomes, the stepdown procedure( Reference Romano and Wolf 36 ) was also applied. This method adjusts the P value associated with the individual permutation tests, yet unlike Bonferroni adjustment methods, it accounts for interdependence across measures. A more thorough description of the permutation and stepdown procedures has been reported elsewhere( 37 ). The present study used permutation tests based on 100 000 replications. For the stepdown procedure, six domains were tested including whether the child met dietary recommendations at each time point for grains, dairy, protein, fruit and vegetables, fatty/sugary foods, and met all dietary recommendations. Two-tailed P values and CI were reported; findings with P<0·05 were interpreted as statistically significant and P<0·10 were referred to as approaching significance. Effect sizes were reported using odds ratios.
Due to differential attrition, the estimation samples may not be representative of the original randomised sample. Attrition refers to participants who dropped out prior to an assessment point and/or those who did not engage in a particular assessment. An inverse probability weighting (IPW) procedure( Reference Johnston and DiNardo 38 ) was applied to address this issue. This involved estimating logistic regression models predicting the probability of completing an interview at each assessment point using a large set of baseline characteristics. Between 8 and 12 % of 138 baseline factors, analysed using bivariate tests, predicted attrition from the intervention group. The corresponding figures for the control group ranged from 15 to 24 %. Characteristics which did not have any missing data and were not collinear with any other characteristics were used to generate the predicted probabilities from the logistic models. These probabilities were then applied as weights in the outcome analyses, so that a larger weight was applied to participants that were under-represented in the sample due to attrition.
Mediation analysis using a counterfactual approach( Reference VanderWeele and Vansteelandt 39 ) was used to test whether the intervention had an indirect effect on cognitive functioning via its effect on meeting dietary recommendations. A mediation effect was identified if the independent variable (treatment status) had a significant effect on the mediator variable (dietary intake) as well as the dependent variable (cognitive functioning), however the effect of the independent variable on the dependent variable was no longer significant when the mediator variable was controlled for. If the effect was reduced but still significant when the mediator variable was included, this is referred to as partial mediation. A regression framework was used to estimate the natural direct and indirect effects( Reference VanderWeele and Vansteelandt 39 ). The natural direct effect represents the effect of treatment on the outcomes through all pathways except via the included mediator. The natural indirect effect represents the amount by which the outcome would change on average if the treatment level was fixed but the value of the mediator variable was changed. Finally, the marginal total effect is the sum of the previous two effects. To determine whether the inclusion of the mediator variable significantly reduced the relationship between the independent variable and the dependent variable, bootstrapping methods were used. All dietary measures on which there was a significant treatment effect and have a theoretical link with cognitive development were considered as potential mediators.
Results
Study participation and baseline characteristics
In total, 233 participants were recruited and randomised to the intervention (n 115) or control (n 118) group. Table 1 shows the comparability of the groups on selected maternal sociodemographic, health, personality and parenting measures, as well as highlighting the disadvantaged status of the cohort. The differences between the intervention and control groups were small in magnitude and consistent with pure chance, which indicates the equivalence of the groups at baseline. Of those randomised, the number completing assessments was 205 at baseline, 165 at 12 months, 154 at 18 months, 165 at 24 months and 149 at 36 months (see Fig. 1). The IPW procedure, described above, accounts for this attrition.
CONSORT diagram of participant flow in the Preparing for Life programme (BL, baseline; 12M, 12-month; 18M, 18-month; 24M, 24-month; 36M, 36-month)
Baseline characteristics of intervention and control groups; Preparing for Life programme, Dublin, Republic of Ireland, 2008–2015
Low education represents participants who left school after they completed a statewide examination at age 15–16 years. Physical health condition indicates whether the mother has ever been diagnosed with any of twenty-two listed conditions. Mental health condition indicates whether the mother has ever been diagnosed with any of eight listed mental health conditions. Intelligence quotient (IQ) was measured 3 months post-birth using the Wechsler Abbreviated Scale of Intelligence (WASI). The Vulnerable Attachment Style Questionnaire (VASQ) assesses respondents’ interactions and dependence on other people. Scores above 15 are indicative of depressive disorders. The Adult Adolescent Parenting Inventory (AAPI) measures approaches to parenting and higher scores indicate a high risk of abuse/neglect. The Pearlin Self-Efficacy Scale ranges from 0 to 4 with higher scores indicating higher self-efficacy. The Rosenberg Self-Esteem Scale ranges from 0 to 18 with higher scores indicating more maternal self-esteem. The Knowledge of Infant Development Inventory (KIDI) represents the percentage of correct responses to questions relating to child development milestones. Higher scores indicate more knowledge of infant development.
Descriptive statistics
Table 2 shows that the proportion of children meeting dietary recommendations increased between 12 and 36 months, which was anticipated given the dietary transition from infancy to toddlerhood. However, the proportion of children consuming fatty/sugary foods also rose. By 36 months, over 60 % were meeting the dietary recommendations for grains and dairy; however, only a third met the protein and fruit and vegetable food group recommendations, and less than a fifth met all dietary recommendations.
Impact on children’s dietary intake between 12 and 36 months of age; Preparing for Life programme, Dublin, Republic of Ireland, 2008–2015
M I, proportion of the intervention group meeting recommendations; M C, proportion of the control group meeting recommendations.
n ranged from 165 at 12 months to 149 at 36 months.
* P<0·05.
† Two-tailed P value from χ 2 test of logistic regression coefficient.
‡ Two-tailed P value from an individual permutation test.
§ Two-tailed P value from a stepdown permutation test. The P values in bold indicate statistical significance.
Effect of intervention on meeting dietary recommendations
Table 2 demonstrates that the P values from the conventional χ 2 tests and the permutation tests were very similar; therefore only the permutation results are interpreted as they are more reliable in small samples and allow us to adjust for multiple comparisons.
There was no treatment effect on meeting grain recommendations at any time point or on meeting dairy recommendations at 18, 24 and 36 months. At 12 months, a greater proportion of the intervention group met dairy recommendations compared with the control group (OR=1·86); however, this finding did not survive the stepdown adjustment. There were no effects on meeting protein recommendations at 12 or 18 months; however, at 24 months a greater proportion of the intervention group met recommendations compared with the controls (OR=2·30). The finding that a greater proportion of the intervention group met protein recommendations at 36 months also approached significance (OR=2·09). In addition, the first stepdown P value in the protein stepdown domain approached significance. There were no effects on meeting fruit and vegetable recommendations at 12, 18 and 36 months; however, at 24 months a greater proportion of the intervention group met recommendations compared with the control group (OR=2·27). The first stepdown P value also approached significance. There were no effects at any time point on the proportion of children eating fatty/sugary food no more than once daily. Finally, there were no effects on meeting all dietary recommendations at 12, 18 and 36 months; however, at 24 months a greater proportion of the intervention group met all dietary recommendations (OR=3·82). The first stepdown P value in the meeting all dietary recommendations stepdown domain also approached significance.
In total, the intervention group had more favourable outcomes compared with the control group on nineteen of the twenty-four (79 %) measures under investigation, which is statistically significantly different from the 50 % we would expect if the programme was having no impact, according to a two-sided binomial test (P=0·007).
Table 3 shows that the conventional χ 2 tests from IPW-adjusted logistic regressions were similar to the IPW-adjusted permutation tests; thus only the permutation tests are interpreted here. The unweighted and IPW-weighted results revealed a similar pattern, yet there were some differences. Specifically, the finding of a greater proportion of the intervention group meeting dairy recommendations at 12 months approached significance in the IPW-weighted analysis, while it met conventional levels of significance in the unweighted analysis. Meeting protein recommendations at 18 months approached significance in the IPW-weighted results, while it was not close to significance in the unweighted analysis. Additionally, the finding for protein recommendations at 36 months, which approached significance in the unweighted analysis, was significant at the 5 % level with the weighted analysis. Finally, the finding for fruit and vegetable recommendations at 24 months in the unweighted analysis approached significance only when attrition was accounted for in the IPW-weighted analysis. As a result, this finding no longer survived the stepdown adjustment.
Inverse probability weighting (IPW)-adjusted impact on children’s dietary intake between 12 and 36 months of age; Preparing for Life programme, Dublin, Republic of Ireland, 2008–2015
M I, proportion of the intervention group meeting recommendations; M C, proportion of the control group meeting recommendations.
n ranged from 165 at 12 months to 149 at 36 months.
* P<0·05.
† Two-tailed P value from χ 2 test of IPW logistic regression coefficient.
‡ Two-tailed IPW-adjusted P value from an individual permutation test.
§ Two-tailed IPW-adjusted P value from a stepdown permutation test. The P values in bold indicate statistical significance.
Following the IPW adjustment, the intervention group had more favourable outcomes on twenty of the twenty-four (83 %) dietary measures, which is more than was found in the unweighted analysis. The difference between the observed and expected proportions under the null hypothesis of no programme effect (50 %) was statistically significant in a two-sided binomial test (P=0·0003).
Multiple imputation was conducted as an alternative to IPW and the results were largely equivalent. Additional analyses controlling for any salient baseline variables also found very similar results. All additional results are available in the online supplementary material, Tables S1 and S2.
Mediating role of dietary intake on cognition
The results in Table 2, in conjunction with existing theoretical evidence, were used to select the potential mediators. Protein intake at 24 and 36 months and fruit and vegetable intake at 24 months were chosen as there is prior evidence linking both to cognitive functioning( Reference Georgieff 7 , Reference Riggs, Chou and Spruijt-Metz 40 ) and a significant effect was found in both stepdown domains. In order to limit the bias associated with mediator–outcome confounders, baseline covariates were included in the analysis which consisted of child gender, whether or not the mother had a state medical card (a proxy for low income), whether or not the mother had low education (did not complete second level) and a measure of the mother’s mental health( 41 ).
The columns in Table 4 represent the three steps of the mediation analysis. In model 1, the regression of cognitive functioning v. the treatment indicator and the baseline covariates was performed. At 24 months, the finding that the cognitive development scores of the intervention group were approximately 4·4 % higher than those of the control group approached significance. At 36 months there was a significant difference at the 5 % level, such that children in the intervention group scored approximately 5 % higher in terms of their cognitive functioning than control children.
Mediation analysis: effect on children’s cognitive functioning (standardised score on Developmental Profile-3: cognitive section (DP-3)) at 24 and 36 months, expressed as unstandardised regression coefficients (b); Preparing for Life (PBL) programme, Dublin, Republic of Ireland, 2008–2015
DP-3 is the dependent variable. Each model includes the baseline covariates (child gender, medical card, low maternal education and maternal mental health). Proportion of effect mediated=proportion of the total intervention effect on DP-3 mediated by meeting protein recommendations.
*P<0·05, **P<0·01.
Model 2 examined the direct impact of the mediators on cognitive functioning. Meeting protein or fruit and vegetable consumption recommendations at 24 months was not significantly associated with cognitive functioning at 24 months. Thus, the final step of the mediation analysis was not conducted for these mediators. In addition, neither of the 24-month diet measures was significantly associated with cognitive functioning at 36 months. However, meeting protein recommendations at 36 months was associated with higher cognitive functioning at 36 months and the coefficient implied that meeting protein recommendations was associated with a 7 % increase in cognitive functioning.
Model 3 included both the independent variable (treatment assignment), the relevant mediator from model 2 (protein at 36 months), a treatment × mediator interaction term and the baseline controls to explain cognitive functioning at 36 months. The addition of protein and the interaction term led to a slight reduction on the treatment assignment coefficient, but it still approached significance, indicative of partial mediation. The significant positive relationship between protein recommendations and cognitive functioning remained. The interaction term was not statistically significant.
Finally, 90 % bias-corrected CI were calculated to assess the statistical significance of the natural indirect, natural direct and marginal total effects of the programme on cognitive functioning at 36 months. A bias-corrected bootstrapped CI was calculated for each effect. The indirect effect at 36 months approached significance according to this bootstrapping test. It was also possible to separate the total effect of treatment assignment on cognitive functioning into two components. The first component was the direct effect, which represents the change in cognitive functioning associated with a change in treatment assignment (holding constant meeting protein recommendations). The second component was the indirect effect, which measures the change in cognitive functioning when treatment assignment remains fixed and meeting protein recommendations changes by the amount it would have changed by had treatment assignment been altered. The direct effect was calculated by examining the effect of treatment on cognitive functioning in model 3 (which controls for protein at 36 months as a mediator). The indirect effect was computed by first examining the effect of treatment on meeting protein recommendations at 36 months and then combining this with the effect of meeting protein recommendations on cognition. In this case, the indirect effect accounted for 13 % of the total effect of treatment on cognitive functioning.
Discussion
The PFL programme had a positive impact on meeting dietary recommendations for protein foods at 24 and 36 months and all food groups at 24 months among children living in a disadvantaged community. Diet was assessed as meeting food-based dietary guidelines for grains, fruits and vegetables, dairy, protein, and consumption of fatty/sugary foods. The intervention group was more likely to meet dietary recommendations across all food groups compared with the control group. The strongest intervention effects were found for the protein food group and overall diet. Mediation analysis indicated that 13 % of the intervention’s effect on cognitive functioning was mediated by protein food consumption at 36 months.
Parents play a major role in determining the quality of their child’s diet by controlling the types, amount and frequency of foods consumed, as well as responding to their children’s food preferences and food refusals. There is evidence in the literature from developing countries for the impact of early intervention programmes on child development and nutrition( Reference Grantham-McGregor, Powell and Walker 42 ). However, HVP targeting child development in developed countries rarely evaluate or report nutrition outcomes, while those focusing on dietary intake fail to include measures of child development. For example, some targeted nutrition interventions in high-income countries adopt a home visiting approach, yet they typically focus on fruit and vegetable consumption or obesity prevention( Reference Haire-Joshu, Elliot and Caito 24 , Reference Wen, Baur and Simpson 25 ). In addition, while traditional HVP report on multiple outcomes (e.g. psychomotor and cognitive development, language development, social development, behavioural problems, child maltreatment, health-care coverage and use, birth outcomes and health behaviours( Reference Avellar and Supplee 19 , Reference Peacock, Konrad and Watson 20 )), only a small number of studies in developed countries have evaluated aspects of nutrition or infant feeding practices. One US study reported increased breast-feeding initiation rates in a sample of home-visited disadvantaged African American mothers( Reference Johnson, Howell and Molloy 21 ). Similarly, the Healthy Steps for Young Children programme reported higher breast-feeding rates and improved breast-feeding practices( Reference Kitzman, Olds and Henderson 22 ). Finally, one older HVP targeting child development in a low-SES community in Ireland reported an intervention effect across multiple food groups including animal protein, non-animal protein, whole foods, vegetables, fruit and milk( Reference Johnston, Huebner and Anderson 23 ).
The results of the mediation analysis, while only approaching significance, are still noteworthy. Research on protein and specifically animal-source food is typically conducted in developing countries where HVP usually involve supplementation( Reference Grantham-McGregor, Powell and Walker 42 ). Therefore changes in nutrient intakes are a result of the provision of foods or supplements rather than changes in parenting practices or knowledge. Additional evidence from observational and intervention studies in low-income countries shows that the consumption of milk and other animal-source foods can improve growth, cognitive function, and reduce the prevalence of nutritional deficiencies( Reference Dror and Allen 43 ). A recent review reported the likely benefits of combining nutrition and child development activities( Reference Grantham-McGregor, Fernald and Kagawa 44 ), and the authors called for more large-scale programmes that integrate stimulation into health and nutrition services and evaluate children’s growth and development.
While the mechanisms underlying the effect of the HVP on protein food intake cannot be determined, the intervention did provide nutrition-related Tip Sheets which may have raised awareness of appropriate foods and eating behaviours. Of the forty-six nutrition Tip Sheets provided, fifteen mentioned protein foods such as meat, fish and eggs; and of those, three targeted protein foods specifically as they encouraged parents to ensure adequate intakes of iron and calcium. Consequently, the protein food group may have been particularly sensitive to the intervention. This sensitivity may relate to the age of the children because, according to the National Preschool Nutrition Survey in Ireland, protein-based food intake typically increases by age 4 years( 45 ).
While the present study contributes to the literature, there are a number of limitations. First, the results are based on one disadvantaged community and may not be generalisable to other areas. Second, eliciting an accurate measure of diet is challenging and all methods have strengths and limitations. Misreporting dietary intake by over- or under-reporting of ‘healthy’ or ‘unhealthy’ foods triggered by sociocultural pressure to follow a ‘correct’ dietary pattern is common( Reference Kipnis, Midthune and Freedman 46 ). Measuring dietary intake of young children or infants is even more difficult as it requires the parent to provide information which is further complicated by the number of people responsible for the child’s food intake( Reference Foster and Adamson 47 ). Differential misreporting may have arisen if parents in the intervention group provided a more favourable assessment of their child’s diet than parents in the control group. In order to assess this issue, a separate study based on the PFL evaluation( 48 ) found that there was no significant difference between the intervention and control groups in terms of social desirable responding as measured by a Social Desirability Scale. Third, although the dietary instrument used in the present study was limited, the questions were based on standard FFQ used in large population-based surveys( Reference Riboli and Kaaks 49 ) and were adapted for assessment of children’s diet( Reference Shrivastava, Murrin and Sweeney 31 ). A further complexity is that diet changes considerably from infancy to early childhood. In Ireland, a national policy exists for infant feeding in the first year of life( 50 ) and Healthy Eating Guidelines exist for children over 5 years( 51 ). However, there are no clear guidelines for children aged 1 to 4 years, other than a publication targeted at pre-school services( 32 ). This makes it difficult to assess if Irish children are meeting dietary recommendations.
A strength of the present study was the methodology used to overcome internal validity issues inherent in randomised controlled trials such as small sample size, differential attrition and multiple testing. First, while the sample size was small, the permutation testing method helped address this issue. Yet the similarity of the findings from the conventional χ 2 tests and the permutation tests suggests that the assumptions underlying the traditional tests may hold in this sample. Second, differential attrition was addressed through the use of IPW. Some important differences between the unweighted and IPW-weighted results were identified, with IPW resulting in more conservative results. This demonstrates the importance of measuring and controlling for differential attrition in experimental trials. Third, studies of HVP typically report many outcomes, yet few account for multiple testing which risks overstating programme impact. The stepdown procedure applied here highlighted the implications of failing to address this issue. That the effects for meeting protein recommendations and all dietary recommendations survived the stepdown procedure increases confidence in these findings. A further methodological strength was the use of bootstrapping techniques to assess the significance of the indirect effects in the mediation analysis. Frequently studies in this field fail to test the significance of reported mediation results.
The findings reported here may have implications for both practice and policy. While over two-thirds of the sample met recommendations for grains and dairy by age 3 years, less than one-third met protein and fruit and vegetable recommendations, and over one-third were eating fatty and sugary foods on a daily basis. This suggests that targeted interventions among low-SES populations are needed to improve dietary patterns early in life. From a policy perspective, the effects for diet and cognitive development may have economic relevance. A cost–benefit analysis of multiple, primarily US-based, HVP found returns ranging from $US 0·21 to $US 30·46 per $US invested, with a median return of $US 1·62( 52 ). The proportion of the return generated from health-care saving amounted to ~10 % and the proportion generated by improvements in labour market and educational outcomes was ~70 %. As the PFL intervention had some an impact on improving diet and cognitive functioning, the intervention may generate similar positive returns in the long run; thus future work should include a cost–benefit analysis. In addition, future HVP studies should evaluate dietary intake, as well as complementary and early childhood feeding practices, while interventions focused on dietary change or obesity prevention should incorporate measures of child development. Finally, studies investigating the effects of combined nutrition–child development interventions are also warranted.
Acknowledgements
Acknowledgements: The authors would like to thank the Northside Partnership who provided funding for the Preparing for Life evaluation through The Atlantic Philanthropies and the Department of Children and Youth Affairs. They are also grateful to all those who participated in and supported this research, especially the participating families and community organisations, the PFL intervention staff and the Expert Advisory Committee. Thanks go also to Professors James Heckman, Colm Harmon, Sylvana Cote, Cecily Kelleher, Sharon Ramey and Craig Ramey for their guidance and advice throughout the project, and the Early Childhood Research Team at UCD Geary Institute for Public Policy for their contributions to the work. Financial support: The trial was funded by the Northside Partnership through The Atlantic Philanthropies and the Department of Children and Youth Affairs. The Northside Partnership had no role in design, analysis, or writing of this article. Conflict of interest: The authors declare that they have no conflicts of interests. Authorship: O.D. designed the overall PFL study. O.D. and A.S. conceived and designed the present article. N.F. did the data analysis. All authors contributed to the interpretation of the data, drafted the article and approved the final version. O.D. is guarantor. Ethics of human subject participation: This study was conducted according to the guidelines laid down in the Declaration of Helsinki and all procedures involving human subjects/patients were approved by the University College Dublin’s Human Research Ethics Committee, the Rotunda Hospital’s Ethics Committee and the National Maternity Hospital’s Ethics Committee. Written informed consent was obtained from all subjects/patients. Trial registration: controlled-trials.com (ISRCTN04631728, http://www.controlled-trials.com/ISRCTN04631728/).
Supplementary material
To view supplementary material for this article, please visit http://dx.doi.org/10.1017/S1368980016001877
