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6 February 2018

17 Pages

Predictors of Dietary Energy Density among Preschool Aged Children

,
,
,
and
1
School of Exercise and Nutrition Sciences, Deakin University, Burwood, VIC 3125, Australia
2
Institute for Physical Activity and Nutrition (IPAN), School of Exercise and Nutrition Sciences, Deakin University, Geelong, VIC 3220, Australia
*
Author to whom correspondence should be addressed.
Nutrients2018, 10(2), 178;https://doi.org/10.3390/nu10020178
This article belongs to the Special Issue Energy Intake, Trends, and Determinants
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Abstract

Childhood obesity is a global problem with many contributing factors including dietary energy density (DED). This paper aims to investigate potential predictors of DED among preschool aged children in Victoria, Australia. Secondary analysis of longitudinal data for 209 mother–child pairs from the Melbourne Infant Feeding, Activity and Nutrition Trial was conducted. Data for predictors (maternal child feeding and nutrition knowledge, maternal dietary intake, home food availability, socioeconomic status) were obtained through questionnaires completed by first-time mothers when children were aged 4 or 18 months. Three 24-h dietary recalls were completed when children were aged ~3.5 years. DED was calculated utilizing three methods: “food only”, “food and dairy beverages”, and “food and all beverages”. Linear regression analyses were conducted to identify associations between predictors and these three measures of children’s DED. Home availability of fruits (β: −0.82; 95% CI: −1.35, −0.29, p = 0.002 for DEDfood; β: −0.42; 95% CI: −0.82, −0.02, p = 0.041 for DEDfood+dairy beverages) and non-core snacks (β: 0.11; 95% CI: 0.02, 0.20, p = 0.016 for DEDfood; β: 0.09; 95% CI: 0.02, 0.15, p = 0.010 for DEDfood+dairy beverages) were significantly associated with two of the three DED measures. Providing fruit at home early in a child’s life may encourage the establishment of healthful eating behaviors that could promote a diet that is lower in energy density later in life. Home availability of non-core snacks is likely to increase the energy density of preschool children’s diets, supporting the proposition that non-core snack availability at home should be limited.

1. Introduction

Childhood obesity is a global problem. The World Health Organization estimated that 42 million children aged five years and under were overweight or obese in 2015, and these rates are expected to rise to 70 million by 2025 if current trends continue [1]. In Australia, approximately one in five children aged between two and four years is classified as overweight or obese [2]. Childhood obesity is associated with wide-ranging health and social risks [3] and it tends to track into adolescence and adulthood, with additional risks of negative health outcomes [3,4].
While the etiology of obesity is complex, energy intakes above energy requirements are a key contributor. One aspect of diet that may be particularly important is dietary energy density (DED), which is the concentration of energy in food or food and selected beverages (kJ/g). A systematic review by the 2010 Dietary Guidelines Advisory Committee in the United States (US) concluded that there was moderately strong evidence from longitudinal cohort studies in children and adolescents of a positive association between DED and increased adiposity [5]. Further, a 2016 meta-analysis demonstrated that DED was directly associated with the risk of excess adiposity among children and adolescents [6]. Short-term experimental feeding studies using covert adjustments of energy density demonstrated that energy density influences young children’s energy intake [7,8,9,10]. Additionally, nationally representative data in the US and large population surveys of children across several European countries showed that young children who consume diets that are lower in energy density have more healthful diets (less fat and sugar; more vegetables and fruits) than peers who consume diets that are higher in energy density [11,12].
The energy density of foods and beverages is influenced by their water content and macronutrient composition. Foods high in water and/or fiber tend to be low in energy density, while foods high in fat tend to be high in energy density. Beverages are generally low in energy density because of their high water content. There are different methods that can be used to calculate DED in order to adjust for the influence of beverages because beverages may disproportionately influence DED values [13]. While there is no consensus on which DED calculation method is most appropriate, calculating DED based on ‘food only’ is recommended for studies examining relationships with body weight [14]. Dairy beverages are part of a healthy diet as recommended by the Australian Dietary Guidelines [15] and provide substantial (12.5%) energy in two- to three-year-old children’s diets [16]. Given this, it is likely to be important to consider dairy beverages (or dairy alternatives) when assessing DED in young children’s diets [17,18].
With increasing evidence indicating that DED influences children’s body weight and energy intakes, it is important to identify the predictors of DED in order to better target and inform childhood obesity prevention interventions. Young children’s diets develop primarily within the family unit, making it vital to examine how family and demographic characteristics may influence DED [19]. The “Ecological model of predictors of childhood overweight” proposed by Davison and Birch in 2001 [20] is useful for identifying family and demographic characteristics as potential predictors of children’s DED. Several potential predictors, including parental nutrition knowledge [21], parental dietary intake [22], home food availability [23], and socioeconomic status [24], have been shown to be associated with various aspects of children’s diets; however, little is known about the predictors of children’s overall DED [11,12,25]. This study aimed to identify the predictors of DED among a sample of Australian preschool children using age-appropriate DED calculation methods.

2. Materials and Methods

2.1. Study Design and Participants

This study was a secondary analysis of data from the intervention and control participants in the Melbourne Infant Feeding, Activity and Nutrition Trial (Melbourne InFANT Program). The Melbourne InFANT Program was a cluster randomized controlled trial designed to test an intervention, where first-time parents were educated by experienced dietitians on how to promote healthy eating and active play in early childhood [26]. The intervention began when the children were 4 months of age and lasted until children were 18 months of age, with further data collection occurring at approximate ages 3.5 and 5 years [27]. A total of 542 families were recruited through Maternal and Child Health (MCH) centers within a 60-km radius from Deakin University, Melbourne, Australia [28]. Participants were equally and randomly assigned to either the intervention or control arm. Data were collected from participants who were English speaking and who provided informed consent. Parents were asked to complete questionnaires about their children and themselves at ages 4, 9, and 18 months and 3.5 and 5 years. Parents were also asked to provide three five-pass 24-h dietary recalls administered by telephone interview to record children’s dietary intakes when children were aged 9 and 18 months [26] and again at 3.5 and 5 years [27]. Dietary recalls were collected by dietitians on three non-consecutive days including a weekend day. Visual aids were provided prior to the interviews to help parents to determine food portion sizes. This is a valid and feasible method to collect dietary data [29,30,31]. The primary outcomes of the Melbourne InFANT Program are reported elsewhere [28]. Ethics approval was provided by Deakin University Ethics Committee (EC 175-2007) and by the Victorian Office for Children (CDF/07/1138). The current study utilized questionnaire data when children were 4 and 18 months and 3.5 years of age as well as the 24-h dietary recall data when children were 3.5 years of age.

2.2. Outcome Measure: Dietary Energy Density

Dietary energy density was assessed using 24-h dietary recall data [13,17] collected when children were approximately 3.5 years of age. Dietary intake data were coded by matching food and beverage items to their nutrient composition using the Australian Food Supplement and Nutrient Database “AUSNUT 2007” which has 4225 food and beverage items [32]. Additionally, the nutrient composition of items not found in the AUSTNUT 2007 database was included and classified according to information from the manufacturing company or the product’s nutrition information panel [28].
Dietary energy density was calculated using multiple age-appropriate methods including beverages most likely to be consumed by preschool aged children; food only (no beverages; DEDfood), food and dairy beverages (DEDfood+dairy beverages) and food and all beverages (included water; DEDfood+all beverages). Specific AUSNUT 2007 food groups were chosen for the DEDfood and DEDfood+all beverages variable calculations considering previously published criteria [13,33]. While previous studies have used a DED variable for ‘food and milk’ [17,18], the variable used in the present study, DEDfood+dairy beverages, included all dairy and dairy-substitute based beverages (e.g., soy, rice, oat beverages), dairy beverage flavorings, infant/toddler formula and breastmilk. More detailed information can be found in Appendix A Table A1, which includes details of the AUSNUT 2007 food codes included and excluded. Energy densities were calculated by dividing the kilojoules consumed by the weight of food (and beverages for DEDfood+dairy beverages and DEDfood+all beverages) consumed using only the items relevant to each DED variable. As three dietary recall interviews were conducted for each child, daily DED values were calculated and averaged across the recalls.

2.3. Predictor Measures

The potential predictors of DED informed by the ecological model of predictors of childhood overweight [20] included: maternal child feeding and nutrition knowledge, maternal dietary intake, home food availability, and socioeconomic status where maternal education was used as a proxy. Maternal child feeding and nutrition knowledge, maternal dietary intake and home food availability were assessed at child age 18 months and maternal education was assessed at child age 4 months but was considered to be a proxy for socioeconomic status at child age 18 months. Table 1 lists the measures and their response options from the Melbourne InFANT Program questionnaires related to the different predictors that were analyzed, alongside the original sources of the measures.
Table 1. List of measures and responses from the Melbourne Infant Feeding, Activity and Nutrition Trial (InFANT) Program questionnaires considered as predictors.
Maternal knowledge of child feeding and nutrition was assessed using 12 questions related to the child feeding and nutrition intervention messages that were promoted in the Melbourne InFANT Program. Using methods similar to Spence et al. [34], correct answers were given a score of one and incorrect responses a score of zero and an overall summary score was calculated with a maximum score of 12. The total score for the 12 items was shown to have an intraclass correlation of 0.73 in test–retest assessments using a separate sample of 51 mothers with children aged approximately 18 months. Because total scores were non-normally distributed, a new dichotomous variable was created grouping mothers scoring at least 11 or scoring less than 11.
Maternal dietary intake was measured using the Cancer Council Victoria food frequency questionnaire (FFQ), Version 3 [35]. The questions included 98 foods and beverages, with responses ranging from ‘never’ to ‘three + per day’. For the present study, only intakes of fruits, vegetables, non-core sweet snacks, non-core savory snacks, and non-core drinks were analyzed because these groups represent major sources of foods in children’s diets and capture both ends of the energy density continuum. New dichotomous variables were created for each of the food groups using methods similar to those of Spence et al. [34]. Fruit consumption was dichotomized as per the Australian Dietary Guidelines [15], with mothers who reported consuming two or more servings per day grouped together and those consuming less than two serves per day grouped together. As few mothers met the Australian Dietary Guideline for vegetables (five servings per day) [15], vegetable consumption was dichotomized at three or more servings per day. Non-core sweet snacks consumption was dichotomized at one or more servings per day and non-core savory snacks consumption was dichotomized at one or more servings per week. Non-core drinks consumption was dichotomized at one or more glasses per day.
Home food availability was measured using seven questions completed by mothers. Four variables were created representing fruits, vegetables, non-core snacks and non-core drinks using methods similar to those of Collins et al. [37]. Vegetable and fruit availability were dichotomized as ‘always’ and ‘never/sometimes/usually’ available. The composite variable for non-core snacks was a summary score of the three items on chocolates or lollies, potato chips or salty snacks and cakes/donuts/sweet biscuits and was treated as a continuous variable with a maximum score of nine. Similarly, the composite variable for non-core drinks was a summary score of the two items on fruit juice and soft/sweetened beverages and was treated as a continuous variable with a maximum score of six.
Maternal education level was self-reported using one question where mothers indicated their highest education level. A dichotomous variable was created grouping mothers with more than or less than university education [38].

2.4. Covariates

Covariates for this study included: child’s sex (data collected through questionnaires completed by child’s parent when child was aged 4 months) and child’s age (data collected for covariate through questionnaires completed by parent when the child was around 3.5 years of age). As data were from both the intervention and control arms of the Melbourne InFANT Program, treatment arm was also used as a covariate. These covariates were included in all bivariate and multivariable linear regression models. The DAGitty program, version 2.3 (http://www.dagitty.net/dags.html) was used to identify additional potential confounding factors for each predictor [39] and these were included in multivariable linear regression analyses as appropriate.

2.5. Statistical Analysis

A total of 261 parent–child pairs participated in data collection when children were approximately 3.5 years of age. Exclusion criteria were applied excluding pairs where the mother was not a first-time mother (8 pairs) and where children had fewer than three five-pass 24-h dietary recalls at 3.5 years (5 pairs). Participants were excluded for missing data on the potential predictors: maternal child feeding and nutrition knowledge (11 pairs), maternal dietary intake (6 pairs), home food availability (1 pair) and maternal education (0 pairs). Further, participants were excluded when children had fewer than three five-pass 24-h dietary recalls at 18 months (18 pairs). Participants whose average energy intake exceeded the average energy intake of 5329 ± 1219 kilojoules by three or more standard deviations (3 pairs) were excluded. After excluding participants according to the above criteria, the final sample was 209 mother–child pairs.
Using IBM SPSS Statistics (version 24, 2016, IBM-SPSS Inc., Armonk, NY, USA), descriptive analysis was conducted to assess participants’ characteristics. Bivariate linear regression models were performed to examine the association between individual predictors and DED with adjustment for covariates including child sex, child age and treatment arm. Multivariable regression models including the previously described potential confounders were conducted to assess independent effects of each predictor on DED. These regression models controlled for DED at child 18 months, thus ensuring any associations seen were not due to baseline diet. The three DED variables were used as continuous outcomes, and separate models were fitted for the three DED measures. STATA statistical software (version 14, 2015, Stat Corp., College Station, TX, USA) was used to perform bivariate and multivariable linear regressions specifying parent groups as random effects to account for clustering.

3. Results

3.1. Sample Characteristics

Overall, children had a mean age of 3.5 ± 0.2 years with a slightly higher percentage of girls compared with boys (51% vs. 49%) (Table 2). There were slightly more children from the intervention arm of the study compared with the control arm (51% vs. 49%). Children had an average BMI z-score of 0.71 ± 0.89 and the average dietary energy intake including fiber was 5266 ± 1110 kJ. Overall, there was an overrepresentation of mothers with university or higher degrees (64%) relative to mothers with less education (36%).
Table 2. Characteristics of children, mothers and homes in the Melbourne InFANT Program.

3.2. Bivariate and Multivariable Linear Regression Analysis

Bivariate linear regressions showed significant associations between DEDfood and maternal intake of fruits and home availability of fruits and non-core snacks (Table 3). Maternal intake of fruits (β: −0.39; 95% CI: −0.69, −0.08; p = 0.012) and home availability of fruits (β: −0.82; 95% CI: −1.35, −0.29, p = 0.002) had inverse associations in both bivariate and multivariable analyses. Home availability of non-core snacks (β: 0.11; 95% CI: 0.02, 0.20, p = 0.016) was positively associated with children’s DED in both bivariate and multivariable analyses.
Table 3. Results of bivariate and multivariable linear regression analyses among children participating in the Melbourne InFANT Program (n = 209) for the predictors and the dietary energy density variable dietary energy density from food (DEDfood).
Linear regressions showed significant associations between DEDfood+dairy beverages and home availability of fruits and non-core snacks and maternal education used as an indicator of socioeconomic status (Table 4). Home availability of fruits (β: −0.42; 95% CI: −0.82, −0.02, p = 0.041) and maternal education (β: −0.24; 95% CI: −0.48, −0.01; p = 0.044) were inversely associated with children’s DED in both bivariate and multivariable analyses. Home availability of non-core snacks (β: 0.09; 95% CI: 0.02, 0.15, p = 0.010) showed positive associations with children’s DED for both bivariate and multivariable analyses.
Table 4. Results of bivariate and multivariable linear regression analyses among children participating in the Melbourne InFANT Program (n = 209) for the predictors and the dietary energy density variable dietary energy density from food and dairy beverages (DEDfood+dairy beverages).
Home food availability of fruits and non-core snacks showed significant associations with children’s DEDfood+all beverages. (Table 5). When bivariate analyses were conducted, home availability of fruits was inversely associated with children’s DED and home availability of non-core snacks was positively associated with children’s DED. However, neither predictor remained significant in multivariable analysis.
Table 5. Results of bivariate and multivariable linear regression analyses among children participating in the Melbourne InFANT Program (n = 209) for the predictors and the dietary energy density variable dietary energy density from food and all beverages (DEDfood+all beverages).

4. Discussion

This study aimed to investigate potential predictors of DED among preschool aged children. There were several significant relationships between the potential predictors and the energy density variables but the most consistent relationships were those between home availability of fruits and non-core snacks with DED, with significant associations found for DEDfood and DEDfood+dairy beverages. Mean DED values were slightly lower for children in the present study than those reported among preschool children in the US [17].
Home availability of non-core snacks was predictive of preschool aged children’s DEDfood and DEDfood+dairy beverages and there was an inverse association between home availability of fruits and DEDfood and DEDfood+dairy beverages. Previous studies have shown the availability of non-core snacks to have a positive association with children’s intake of non-core snacks [43,44]. Systematic reviews of older children (4–12 years, 6–11 years and 6–18 years) and studies among preschool children have also shown positive associations between home availability of fruits and children’s fruit consumption [45,46,47,48]. Consuming non-core snacks is problematic as it can reduce children’s dietary quality by increasing their intakes of fats and sugars [49]. Children’s preferences for non-core foods could also lead to consumption of these foods over core foods when both are available at home [39]. Therefore, it may be important to covertly restrict the availability of non-core snacks in order to moderate DED and promote intakes of fruits and vegetables [50]. Parents should promote healthy home food environments by favoring core foods over non-core foods from early in a child’s life.
Maternal dietary intakes of vegetables, non-core sweet or savory snacks and non-core drinks did not predict children’s DED. One exception was maternal intake of fruits, which was inversely associated with children’s DED food. Several studies have identified positive associations between parents’ and children’s fruit and vegetable intakes [51,52,53]. The lack of significant results for maternal intake of vegetables, non-core sweet or savory snacks and non-core drinks and children’s DED could be due to differences in how dietary data were collected (three 24-h dietary records for children and food frequency questionnaires for the past 12 months in mothers). It could also be the case that the diet of the father may be important when it comes to some specific foods. Another study using data from the Melbourne InFANT Program found that fathers’ intakes of fruits, sweet snacks and sweetened beverages when children were 20 months of age were associated with children’s intakes of fruits, sweet snacks and sweetened beverages between 20 months and 3.5 years [54]. It is important to note that DED could be influenced by paternal factors, as studies have found that father’s dietary intake of non-core snacks influenced children’s consumption of non-core snacks [51,54]. Further studies should consider examining the association between paternal dietary intakes and children’s DED.
Maternal education was inversely associated with children’s DEDfood+dairy beverages, which is consistent with previous research demonstrating that children from lower socioeconomic positions tend to have less healthful diets [55] and children of mothers with higher maternal educational levels tend to consume lower quantities of non-core snacks and more healthy snacks [25]. Kant and Graubard found that the education level of the household head, but not household income, was related to DEDfood (the only DED variable used) for a nationally representative sample of two- to five-year-old children in the US. This suggests family education level may be more important in determining food choices and, therefore, future intervention studies should target increasing education-related knowledge gaps in target populations [25]. Future research should consider using more than one proxy measure to examine socioeconomic backgrounds when examining children’s DED [56,57].
DEDfood and DEDfood+dairy beverages tended to have similar values and similar associations with the potential predictors compared with DEDfood+all beverages. It has been suggested that DED should be calculated without the inclusion of beverages (e.g., “food only”) when focusing on the risk of obesity, as beverages tend to dilute energy densities leading to misinterpretation of results [58,59,60]. Also, since beverages tend to have lower energy densities (higher water content than macronutrient content) and different levels of satiety in comparison with food items (higher macronutrient content than water content), including beverages in energy density calculations can have a strong effect on overall energy density values. It is also important for researchers to agree on which beverages to include/exclude in DED calculations when examining the diets of preschool aged children.
The present study has several strengths, including the use of longitudinal data to identify the associations between multiple early life predictors that could influence the DED of preschool aged children. Dietary energy densities were calculated using three five-pass 24-h dietary recalls, which is the method recommended as the gold standard [29]. Also, this study used multiple DED variables and previously published measures to obtain data on the potential predictors and careful consideration was given to the potential confounders included in multivariable linear regression models. Limitations of this study include that the majority of the Melbourne InFANT Program mothers were highly educated with high child feeding and nutrition knowledge, which may limit the generalizability of results. Further, the diversity of dietary patterns that exists among preschool children [61,62] may not have been captured in the present study. All measures were self- or parent-reported, which could potentially increase social desirability bias and the exclusion of mothers with missing data for the potential predictors may have influenced the statistical analysis. Only mothers’ diet was considered a predictor in these analyses, but other potentially important role models of eating, including fathers, grandparents, carers and siblings, could also be influential. Lastly, there may be other relevant predictors that were not included in the present study, such as food accessibility [20] and food availability at child care, that could influence young children’s DED.

5. Conclusions

Home availability of fruits and non-core snacks influenced the DED of preschool aged children. This suggests that providing fruit at home early in a child’s life may encourage the establishment of healthful eating behaviors that could promote a diet that is lower in energy density later in life. Children from homes where non-core snacks were readily available early in life were more likely to consume diets that were higher in energy density even when their mothers had relatively high nutrition knowledge and educational backgrounds. Mothers should be advised to limit the presence of non-core snacks at home early on in their child’s life.

Acknowledgments

The Melbourne InFANT Program was funded by contributions by Deakin University, the Australian National Health and Medical Research Council (NHMRC) (grant nos. ID1008879 and ID425801), the National Heart Foundation of Australia, and the Victorian Health Promotion Foundation. S.A.M. is supported by an NHMRC Career Development Fellowship Level 2, ID1104636 and was previously supported by an ARC Future Fellowship (2011–2015, FT100100581).

Author Contributions

K.E.L. and S.A.M. were responsible for the study conception. K.J.C. and S.A.M. were responsible for dietary data collection in their lead investigator roles in the Melbourne InFANT Program. N.N.T.F. wrote the manuscript and performed the data analysis. M.Z., K.E.L. and K.J.C. assisted with data analysis. K.E.L., K.J.C., M.Z. and S.A.M. provided significant consultation and made significant contributions to the manuscript.

Conflicts of Interest

The authors declare no conflict of interest.

Appendix A

Table A1. The food groups that were included and excluded in calculating the three DED variables identified via the AUSTNUT 2007 two-digit, three-digit and five-digit food codes 1,2.

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