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Dietary Intake of Polyunsaturated Fatty Acids Among Breast-feeding and Non–breast-feeding 24- to 48-month-old Children in Bangladesh

Yakes, Elizabeth A*†; Arsenault, Joanne E; Islam, M Munirul§; Ahmed, Tahmeed§; German, J Bruce; Drake, Christiana*; Hossain, Mohammad B§; Lewis, Bess L||; Rahman, Ahmed Shafiqur§; Jamil, Kazi M§; Brown, Kenneth H*

Journal of Pediatric Gastroenterology and Nutrition: March 2011 - Volume 52 - Issue 3 - p 351–359
doi: 10.1097/MPG.0b013e3182042bc8
Original Articles: Hepatology and Nutrition

Objective: The aim of the study was to assess the adequacy of polyunsaturated fatty acid intake by rural Bangladeshi children 24 to 48 months old in relation to their breast-feeding status.

Materials and Methods: Multistage sampling was used to select a representative sample of children 24 to 48 months of age from 2 rural districts in Bangladesh (n = 479). Two nonconsecutive 24-hour periods of dietary data were collected via 12-hour daytime in-home observations and recall. Breast milk intake was estimated using test weighing. The National Cancer Institute (NCI) method for episodically consumed foods was used to estimate distributions of usual food and nutrient intakes.

Results: Based on the estimated intake distributions, >95% of the children had usual fat intakes <30% of total energy. Among 24- to 35-month-old (younger) and 36- to 48-month-old (older) children, respectively, 4% and 16% of breast-feeding children and 31% and 41% of non–breast-feeding children were estimated to consume <10% of total energy from fat. An estimated 80% of all of the children consumed <4% of total energy as linoleic acid, and 99% consumed <1% of energy as α-linolenic acid. Younger breast-feeding children had higher estimated average docosahexaenoic acid (DHA) intakes (0.04 g DHA/day) than their non–breast-feeding counterparts (0.01 g DHA/day; P = 0.0005). Both breast-feeding and non–breast-feeding older children had estimated mean DHA intakes of 0.02 g/day (P = 0.74).

Conclusions: Rural Bangladeshi children 24 to 48 months old, and especially those who have discontinued breast-feeding, may benefit from increased fat consumption.

*Graduate Group in Epidemiology, Bangladesh

Department of Nutrition, Bangladesh

Department of Food Science and Technology, Bangladesh

||International Agricultural Development Graduate Group, Bangladesh

§International Centre for Diarrhoeal Disease Research, Bangladesh (ICDDR,B) Dhaka, Bangladesh.

Received 11 July, 2010

Accepted 28 October, 2010

Address correspondence and reprint requests to Elizabeth Yakes, Department of Nutrition, University of California, One Shields Avenue, Davis, CA 95616 (e-mail:

This study was supported by the Bristol-Myers Squibb Foundation, Inc, the Harvest Plus Challenge Program (coordinated by the Centro Internacional de Agricultura Tropical [CIAT] and the International Food Policy Research Institute [IFPRI]), the National Institute of Environmental Health Sciences (NIEHS) grant R37 ES02710, the NIEHS Superfund Basic Research Program P42 ES04699, the University of California Davis Center for Children's Environmental Health, NIEHS grant P01 ES11269, and the University of California Discovery Program.

The authors report no conflicts of interest.

Young children require adequate amounts of the polyunsaturated fatty acids (PUFAs) linoleic acid (LA), α-linolenic acid (ALA), arachidonic acid (ARA), and docosahexaenoic acid (DHA) for normal growth, development, and immune function (1–6). In particular, LA and ALA are considered to be essential fatty acids (EFAs), because they cannot be synthesized by humans. Adequate fat intake also facilitates the absorption of fat-soluble vitamins and increases the energy density of the diet to allow children to meet their energy needs (7).

The levels of fat intake needed to promote optimal health and development in children have not been conclusively determined. The Joint WHO/FAO Expert Consultation on Fats and Fatty Acids in Human Nutrition and the US Institute of Medicine both recommend that preschool-age children consume ≥30% of total energy as fat, ≥4% of total energy as LA, and ≥1% of energy as ALA (8,9). Others have estimated that children need to consume ≥1% of total energy as LA and ≥0.2% of energy as ALA to prevent EFA deficiency (10–12).

Breast milk is an important source of fat for young children in developing countries, as shown in dietary studies of children younger than 2 years of age in Bangladesh and The Gambia (7,13). For children in many developing countries, fat intake begins to decline with the introduction of complementary foods, which are generally lower in fat than breast milk, and then often drops off sharply when breast-feeding is stopped (7,14,15). Little data are available, however, on fat and PUFA intakes among older preschool-age children in developing countries (9,15).

In Bangladesh, about 78% of children still receive some breast milk at 24 months of age (16). In a study in the late 1970s, Brown et al found that 18- to 30-month-old rural Bangladeshi children had an average intake of about 25% to 28% of total energy from fat (13). We hypothesized that breast milk would continue to be an important source of fat in the diet of 24- to 48-month-old breast-feeding children, with breast-feeding children having a higher intake of fat compared with non–breast-feeding children throughout the age range.

This article examines dietary data from rural Bangladeshi children 24 to 48 months of age. Our aims were to compare the fat and energy intakes of breast-feeding and non–breast-feeding children and to assess the adequacy of their fat intake in relation to current international guidelines. We hypothesized that breast-feeding children would have higher and more adequate fat intakes compared with non–breast-feeding children. We also examined factors that may influence child fat intake, such as child sex, maternal educational level, socioeconomic status (SES), and site of residence, to assist with targeting future interventions.

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Study Design

The study was designed as a cross-sectional, representative, multistage sample survey of children 24 to 48 months of age who resided in 1 of 2 rural districts of the northern poverty belt of Bangladesh. The study protocol was approved by the institutional review board of the University of California, Davis, and the research and ethical review committees of the International Centre for Diarrhoeal Disease Research, Bangladesh (ICDDR,B). Written informed consent was obtained from the parents of all of the participants.

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Data Collection and Processing

Our sampling methods have been previously described in detail (17). Briefly, a multistage cluster sampling design was used to select 480 households with a child 24 to 48 months of age in Trishal and Pirgacha, two upazilas (administrative districts) with a total population of 667,500 and a high prevalence of poverty and food insecurity. Twenty-four clusters (mauzas or villages) were selected from each study site using systematic sampling with probability of selection proportional to estimated population size. At the second stage of sampling, 10 households within each cluster were selected using a global positioning system sampling method (18). Approximately 92% of the originally selected eligible households agreed to participate in the study. Data were collected from 240 households in Trishal from October 2007 to May 2008 and from 240 households in Pirgacha from January to June 2008. Forms for 1 household in Trishal were lost during transit from the field site to ICDDR,B.

Two nonconsecutive days of dietary data were collected via a combination of 12-hour in-home observations and maternal recall of nighttime dietary intake. During daytime observations, a field worker used a frequently standardized food scale (± 1 g, MyWeigh KD7000, MyWeigh, Phoenix, AZ) to measure the weights of all of the foods as they were prepared and consumed, with separate weights obtained at the point of consumption for animal-source foods (ASF) included in recipes. Child breast milk intake was estimated by the test-weighing procedure (19). Children were weighed using an electronic infant balance (±5 g; Seca Baby Scale Model 727, Hamburg, Germany) before and after each breast-feeding episode during the 12-hour observation period, and the total observed duration of breast-feeding episodes was recorded. Insensible water losses were estimated by weighing the child at the beginning and end of a 30-minute nonfeeding period; the average insensible loss value for all of the children (0.0465 g/kg body weight/min) was used to adjust the 12-hour breast milk intakes for insensible losses. The 24-hour intake of breast milk was calculated for each child by summing the differences in body weights from each daytime feeding episode (adjusted for insensible losses) and then extrapolating to 24-hour intake by multiplying the number of feeding episodes reported during the nighttime recall period by the child-specific average amount of breast milk per daytime feed. Children who were experiencing caregiver-reported symptoms of illness on 1 or more observation days were not excluded from dietary observation. Episodes of illness are common for Bangladeshi children, and the data would not reflect children's usual dietary intake if sick children were excluded. The most commonly reported symptom was cough (20.6% of observation days), followed by fever (8.1%), difficulty breathing (2.3%), diarrhea (3 or more liquid/semiliquid stools; 1.6%), and vomiting (0.7%).

Foods consumed were converted into nutrients using the USDA Nutrient Database for Standard Reference (Release 20) and the International Minilist (20,21). Average values for breast milk fatty acids were determined by analyzing the fatty acid composition of actual samples of breast milk from a subset (n = 98) of the children's mothers (22). Women were brought to a central collection site early in the morning and were asked to breast-feed their children. One hour later, breast milk samples (∼3.5 mL) were collected via hand expression from the last breast suckled during the previous feed (23). Breast milk samples were stored in a freezer (−20°C) with a backup generator for 1 week to 6 months (depending on date of collection) until being shipped to ICDDR,B and then UC Davis on dry ice. At UC Davis, the samples were stored at −80°C until extraction and derivatization. A sample of 30-μL (∼0.03 g) human milk was used for fatty acid methyl ester (FAME) analysis. The Folch method was used for lipid extraction (24). FAMEs were separated via capillary gas chromatography using an Agilent Technologies (Santa Clara, CA) gas chromatograph model 7890 equipped with a 30-m DB225MS capillary column (J&W Scientific, Folsom, CA) and a flame ionization detector. An authentic GLC reference standard (461, Nu-Chek Prep, Elysian, MN) and Agilent Technologies GC ChemStation software were used to identify and quantify the FAME peaks. On average, 4.01 mg LA, 0.12 mg ALA, 0.23 mg ARA, and 0.15 mg DHA were delivered per gram of breast milk. The median value for total breast milk fat (3.5 g/dL) was determined by taking the median sum of the laboratory analyzed values for fatty acids and then using a conversion multiplication factor of 1.05 to determine net fat (triacylglycerol equivalents) (25). Food sources of nutrients were obtained by summing the total nutrient intakes for all of the observation days, summing the nutrient intakes from each food source, and calculating the percentage of total nutrient intake from each food.

Two height and weight measurements were collected from all of the children using a portable stadiometer (±0.1 cm; ShorrBoard measuring board, Olney, MD) and frequently standardized electronic scale (± 5 g; Seca model 727, Hamburg, Germany). If 2 height measurements differed by more than 0.5 cm, a third height measurement was taken. z Scores were calculated using the SAS (version 9.2, SAS Institute, Cary, NC) macros for the WHO Child Growth Standards (26). Data on SES were collected via a maternal interview.

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Data Analysis

We used the NCI method for episodically consumed foods to estimate distributions of usual food and nutrient intake (27,28). This method was used to better approximate the variance of the intake distributions by removing within-person variation and to improve estimates of intake for foods and nutrients that were episodically consumed in the study population during the 2 days of dietary data collection. Briefly, the NCI method for episodically consumed foods uses data from 2 or more 24-hour estimates of intake in a 2-part model that first estimates the probability of consumption using logistic regression, and then estimates the amount consumed using linear mixed regression on a transformed scale (27).

Our covariates of interest for both the probability of consumption and amount of consumption models included child sex and breast-feeding status, maternal education level, household access to electricity and housing quality, season, and site of residence. The housing quality variable is a composite continuous measure assessing the type of floors, walls, and sanitary facilities in the family home and the main type of cooking fuel used. Maternal education was a continuous variable that was categorized to minimize the effects of measurement error.

The first model (probability of consumption) was of the form:

The second model (amount of consumption) was of the form:

Both models were used to estimate distributions of intake for foods and nutrients that were episodically consumed, including oil, egg, fish, meat/poultry, ARA, EPA, and DHA. Only the amount model was used for all of the other foods and nutrients that are presented because they were consumed in some amount by all of the participants on all of the observation days. Percentages of energy derived from fat, carbohydrate, and protein were calculated for each child-day; these distributions estimate the long-term mean of the daily ratio of intakes (the usual ratio of intakes) (see Freedman et al (29) for in-depth discussion of this concept). Distributions of intakes were estimated for all 24- to 35-month-old (n = 221) and 36- to 48-month-old (n = 236) children who had complete covariate information, and for the breast-feeding and non–breast-feeding subgroups. Covariates were assessed as being significantly associated with intake based on test statistics from the fitted models.

The SURVEYLOGISTIC procedure in SAS (version 9.2) was used to analyze relations between child characteristics and breast-feeding status, and the SURVEYREG procedure was used to analyze relations between child characteristics and z scores for the anthropometric measures. These procedures allow for correct estimation of standard errors and test statistics in survey samples.

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Characteristics of Children and Study Households

Table 1 presents the characteristics of the children included in the study sample and their households by age and breast-feeding status groups. There were slightly more boys than girls in the sample, and approximately half of the children were currently breast-feeding. Overall, 55% of children were stunted (height-for-age z score <−2 SD), 12% were wasted (weight-for-height z score <−2 SD), and 43% were underweight (weight-for-age z score <−2 SD). About 40% of their mothers had never attended a school, and 70% of their households did not have access to electricity. Households were surveyed during the pre-Aman harvest (October–November; 8%), the post-Aman harvest (December–March; 50%) and the Aus/Boro harvest (April–June; 42%).



Bivariate relations between child breast-feeding status and the covariates of interest were examined within age groups (Table 1), and breast-feeding status was not significantly associated with child sex, maternal education, household electricity access or housing quality, season of data collection, or district of residence in either age group. Child anthropometric status was associated with breast-feeding status. In the younger age group, breast-feeding children had a higher prevalence of wasting (15% vs 4%; P = 0.08) and underweight (45% vs 32%; P = 0.06) than non–breast-feeding children, but there was no difference in stunting prevalence. In older children, there were no differences in wasting and underweight prevalence, but breast-feeding children had a higher prevalence of stunting (62% vs 51%; P = 0.03) than non–breast-feeding children.

The relation between child anthropometric status and breast-feeding status was examined in multivariate models. On average, non–breast-feeding children in the older age group had a height-for-age z score that was significantly higher than breast-feeding children (β = 0.43, P = 0.003), after adjusting for child sex, household SES, maternal education, season, and district of residence. After adjusting for those factors, the differences in prevalence of wasting and underweight were no longer significantly associated with breast-feeding status for children in the younger age group.

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Energy Intake and Macronutrient Profile of Diet

Table 2 shows estimated distributions of usual energy intake and usual macronutrient and EFA intake, expressed as a percentage of total energy. The macronutrient distribution of the diet differed based on breast-feeding status, with breast-feeding children within each age category consuming significantly fewer carbohydrates and protein and significantly more total fat as a percent of total energy after adjusting for season, SES, maternal education level, site of residence, and sex in separate linear mixed regression models. In separate models of the same form, intake of EFA as a percentage of energy did not differ significantly by breast-feeding status, except that breast-feeding children in the younger age group consumed significantly more LA as a percentage of total energy than their non–breast-feeding counterparts. Table 3 presents the estimated percentage of children who consumed less than the recommended cutoffs for the fat-to-energy ratios.





In the previously mentioned models for both age groups, better housing quality was consistently associated with higher intakes of protein (younger age group: β = 0.06, P = 0.002; older age group: β = 0.03, P = 0.08), total fat (younger: β = 0.31, P = 0.009; older: β = 0.18, P = 0.01), LA (younger: β = 0.14, P = 0.02; older: β = 0.20, P = 0.004), and ALA (younger: β = 0.20, P = 0.002; older: β = 0.19, P = 0.006), and lower intake of carbohydrates (younger: β = −0.98, P = 0.001; older: −0.84, P = 0.004) as a percentage of total energy. Higher maternal education level was also consistently associated with higher intakes of total fat (younger: β = 0.28, P = 0.04; older: β = 0.13, P = 0.05), LA (younger: β = 0.20, P = 0.008; older: β = 0.15, P = 0.03), ALA (younger: β = 0.18, P = 0.02; older: β = 0.14, P = 0.04), and lower intake of carbohydrates (younger: β = −0.68, P = 0.05; older: −0.69, P = 0.02) as a percentage of total energy. Older children in Trishal had a significantly higher intake of carbohydrates (β = 1.4, P < 0.0001) and a lower intake of total fat (β = −0.38, P < 0.0001), LA (β = −0.46, P < 0.0001), and ALA (older: β = −0.30, P = 0.0001) as a percentage of total energy than older children in Pirgacha.

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Consumption of Fatty Acids

Table 4 presents the children's estimated distributions of usual fat intake. Compared with non–breast-feeding children, breast-feeding children had significantly higher intakes of total fat, saturated fat, monounsaturated fat, ARA, and DHA in the younger age group and total fat, monounsaturated fat, and ARA in the older age group, after adjusting for season, SES, maternal education level, site of residence, and sex. ALA intake, however, was significantly lower in breast-feeding versus non–breast-feeding children in both the younger and older age categories. Associations between other variables in the models and fat intake reflected those observed in the models of fat intake as a percentage of total energy, with a consistent positive association between better housing quality and higher maternal education level and intakes of total fat and polyunsaturated fats and a negative association between living in Trishal versus Pirgacha and intakes of total fat and polyunsaturated fats, after adjusting for the other covariates.



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Food Sources of Fatty Acids in the Diet

For breast-feeding children, breast milk was the greatest source of fat, supplying about one fourth of total fat intake. Additional fat was provided by vegetable oil (22%), snacks/biscuits (13%), and rice (8%). ASF, including freshwater fish, eggs, meat/poultry, and dairy products, provided about 22% of total fat intake for breast-feeding children. For non–breast-feeding children, vegetable oil was the primary source of fat, providing about 35% of total fat intake. Additional fat was provided by snacks/biscuits (14%) and rice (13%). ASF provided about 27% of total fat intake for non–breast-feeding children.

For both breast-feeding and non–breast-feeding children, vegetable oil, snacks/biscuits, and rice accounted for about 70% of total PUFA intake (Fig. 1). Breast milk provided 14% of PUFA intake for breast-feeding children. For both breast-feeding and non–breast-feeding children, egg and freshwater fish provided 80% to 90% of the ARA consumed. Human milk (for breast-feeding children) and meat/poultry provided the remaining 10% to 20%. In contrast, breast milk was the most prominent source of DHA for breast-feeding children, providing around 50% of total DHA. The remaining 50% was supplied by freshwater fish and egg. For non–breast-feeding children, almost all of the DHA was provided by freshwater fish and egg.



Estimated usual intake distributions for food sources of PUFA (g/day) are shown in Table 5. Estimated intake amounts of fish, egg, meat/poultry, soybean oil, and mustard oil did not differ by breast-feeding status in either age group after adjusting for season, SES, maternal education level, sex, and site of residence in separate linear mixed regression models. In these models, better housing quality (β = 0.27; P = 0.05) and higher maternal education level (β = 0.33; P = 0.04) were associated with higher soybean oil intake, and egg intake amount was higher in Pirgacha than in Trishal (β = 1.8; P = 0.002).



In models of the same form that examined probability of intake, the probability of consuming soybean oil was higher in Pirgacha (β = 2.3; P < 0.0001), whereas the probability of consuming mustard oil was higher in Trishal (β = 1.2; P < 0.0001). Children in Trishal had a higher probability of fish intake than children in Pirgacha (β = 0.58; P = 0.002). In contrast, children in Pirgacha had a higher probability of consuming meat/poultry (β = 1.3; P = 0.0002) and egg (β = 1.1; P < 0.0001) than children in Trishal.

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Our data provide additional support for the observation that the fat intake of children in developing countries decreases as breast milk is displaced from the diet (7,14,15). Overall, all of the children 24 to 48 months old were consuming a low-fat, high-carbohydrate diet. Both younger and older breast-feeding children had significantly higher fat intake as a percentage of total energy when compared with their non–breast-feeding counterparts in the same age category. Breast-feeding children in the 24- to 35-month-old age group had the highest mean fat intake as a percentage of total energy at 19.5%. Almost all of the children in the study, however, had fat intakes below the recommended usual intake of 30% of total energy. In general, children from households with better housing quality and more educated mothers had higher fat intake. Fat intakes were also higher in older children living in Pirgacha versus Trishal. However, the average absolute differences were small, and the diets of all of the children were low in fat.

Of particular concern is the large percentage of children who were estimated to be consuming a very low fat diet (<10% of total energy from fat). It was estimated that 30% to 40% of all non–breast-feeding children and 16% of older breast-feeding children had fat consumption below this level. Prentice and Paul considered this to be a very low level of fat intake in children that was “not widely prevalent,” even in the developing world (7).

Most children had EFA intakes that were less than the lower levels recommended by FAO/WHO and the US IOM, but greater than the absolute minimum levels estimated to prevent EFA deficiency (8–12). Although intake of EFA was low, most children had LA:ALA intake ratios that fell within the recommended range of 5:1 to 10:1 (9). Breast-feeding children in both age groups had a lower intake of ALA compared with non–breast-feeding children; this is most likely because of the low ALA levels found in the breast milk samples from the women in this study.

A few other studies have examined fat intake in preschool-age children, and in general, children in this study had lower levels of total fat and EFA intake and similar levels of long-chain fatty acid intake. All of the groups of children in this study had estimated mean intakes of fat as a percentage of total energy that were much lower than the 34.6% reported by Innis et al for 25- to 36-month-old Canadian children (30). One- to 5-year-old rural Chinese children were estimated to consume 21% to 24% of total energy from fat, which is similar to that observed for breast-feeding children in our study, but still much higher than that observed for non–breast-feeding children (31). Absolute LA and ALA intake for Bangladeshi children were similar to those observed for the Chinese children (∼2 g LA/day and ∼0.3 g ALA/day), but less than half of the ranges of intake observed for LA (∼6–9 g/day) and ALA (∼0.7–2 g/day) in the diets of preschool-age children from Australia, Canada, and Belgium (30–33). Interestingly, the ARA and DHA intake of the Bangladeshi children was within the general range observed for children from the studies in Canada, China, Australia, and Belgium (0.02–0.26 g ARA/day and 0.02–0.1 g DHA/day) (30–33). All of these studies used different dietary intake methodology and food composition databases, so there may be some limitations to these comparisons.

Important sources of fat for the children in our study included vegetable oil, rice, and locally produced and prepackaged snacks and biscuits. ASF provided about one fourth of total fat for young children. The probability of consuming different types of oil and ASF varied by district of residence, indicating that local preferences and availability must be taken into account when planning food-based interventions. In both sites, breast milk was a significant contributor to fat intake in breast-feeding children. In particular, it was an important source of DHA. Younger breast-feeding children consumed significantly more DHA than their non–breast-feeding peers. In older children, however, breast milk consumption was not associated with higher DHA intake, most likely because the amount of breast milk consumed is lower in this age group.

Overall, the prevalence of stunting for children in this study was high and in agreement with the 2007 Bangladesh Demographic and Health Survey, which found that 53% to 54% of 24- to 47-month-old children were stunted (16). It is important to note, however, that this is a cross-sectional study, and we cannot establish a causal relation between low fat intake and growth in these children. Although breast-feeding children generally had higher fat intakes, children in the older age group had significantly lower height-for-age z scores compared with their non–breast-feeding counterparts after adjusting for several potential confounders. There was a trend for lower energy intake in breast-feeding versus non–breast-feeding children, but the difference was not significant in either age group after adjusting for other factors. It is possible that there was a nutrient other than energy or fat that was growth limiting in breast-feeding children (7). The negative association between breast-feeding and height-for-age z score may also be due to reverse causality if mothers are less likely to stop breast-feeding a child in poor health, as has been previously described by Marquis et al in Peru (34).

One strength of our study was that we collected quantitative data on daytime consumption via direct observation and weighing of foods and test weighing of breast-feeding children. Another strength is that we used statistical methods developed by the NCI to account for episodic consumption of foods and nutrients and to remove within-person variation from our estimated usual intake distributions.

It is possible, however, that we may have under- or overestimated fat intakes in these children. Children did have some food intake that was estimated via recall, although their main meals were generally consumed during the 12-hour in-home observation period. The mean contribution of energy from the recall period for the children was low (65 kcal/day). To improve maternal recall of child intake, field workers used locally developed standardized plates, cups, and spoons to assist with portion size estimation and a multiple-pass method to minimize omissions. It is possible that mothers may not have witnessed some of their children's food intake because children often moved between households and relatives. However, children were more likely to be in the home with the mother during the early morning and evening periods that the recall covered. Another potentially significant source of error is the conversion of food intakes to nutrient intake using food composition data. The nutrient composition of foods can vary significantly by geography and season, and budgetary constraints prevented us from directly analyzing foods from the study area to determine their fatty acid composition. To partially address this, we have presented quantitative data on food intake to support the nutrient intake data.

Some potential problems with estimating fat intake were specific to breast-feeding children. Breast milk samples were not available from the mothers of all of the breast-feeding children in the study, so values for total fat and individual fatty acids in breast milk were based on the average composition of the samples that were analyzed from a subset of the mothers (n = 98). Ideally, we would have been able to analyze samples from all of the mothers, because the breast milk fatty acid composition can vary considerably based on maternal diet. Our estimated median total fat content of the milk (3.5 g/dL) was within usually reported concentrations internationally, but may be inappropriately high given that the breast-feeding mothers in the present study were generally lean (42% had a BMI <18.5) (22). It is possible that this relatively high fat content is a result of using a spot sample to estimate total breast milk fat content. It has been shown previously that the total fat content of fore- and hind-milk differs (35), so spot samples taken later in the feed may have contained unrepresentatively high fat concentrations. In contrast with the present results, the mean fat content of breast milk at 8 months postpartum was just 2.8 g/dL among similarly nourished Bangladeshi mothers included in an earlier study that used full milk expression (36). If our value for the total fat content of milk was too high, we may have overestimated the fat intake of breast-feeding children. Therefore, we also estimated the distribution of fat consumption as a percentage of total energy using a lower value for breast milk fat content (2.8 g/dL), and found that using a lower mean fat content for the breast milk had only a small effect, increasing the percentage of breast-feeding children whose fat consumption was below 10% of total energy: from 4% to 6% in the younger age group and from 16% to 20% in the older age group. It should be noted that the fatty acid composition of breast milk can be reliably determined from a spot sample (35).

It is also possible that we may have under- or overestimated the intake of breast-feeding children because we extrapolated mean daytime intakes (amount per feed) of breast milk to nighttime feeds. Due to logistical and safety issues, we could not do any test weighing at night, so we do not know whether our assumption for extrapolation of daytime to nighttime amount per feed is correct. It is possible that preschool-age children consume more milk at night than during the day because food consumption displaces breast milk intake during the day.

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Both breast-feeding and non–breast-feeding 24- to 48-month-old Bangladeshi children have fat intakes below the levels recommended by FAO/WHO and the US IOM. It is possible that preschool-age Bangladeshi children could benefit from increased fat intake. This would need to be achieved without reducing the micronutrient density of the diet (37). Thus, studies of lipid-based multiple micronutrient supplements should be considered in this population. It is important that these studies be tied to biochemical and functional outcomes to better inform fat intake requirements for children in this age group. Finally, it is likely that Bangladeshi children would also benefit from an enhanced EFA profile in breast milk if the fatty acid profile of the maternal diet were improved.

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The authors thank the study participants who welcomed us into their homes and the staff from ICDDR,B who were instrumental to the data collection process. We are also grateful to Dr Daniel Tancredi from the UC Davis School of Medicine, Department of Pediatrics, for statistical consultation. The authors’ responsibilities were as follows—E.A.Y.: study design, study implementation, data analysis, interpretation of results, and manuscript preparation; J.E.A.: study design, study implementation, and critical review of manuscript; M.M.I.: study implementation and critical review of manuscript; T.A.: study implementation and critical review of manuscript; J.B.G.: interpretation of results and critical review of manuscript; C.D.: critical review of manuscript; M.B.H.: study implementation and critical review of manuscript; B.L.L.: study design and study implementation; A.S.R.: study implementation and critical review of manuscript; K.M.J.: study implementation and critical review of manuscript; K.H.B.: funding, study design, interpretation of results, and critical review of the manuscript.

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breast-feeding; docosahexaenoic acid; polyunsaturated fatty acid

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