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Prevalence and determinants of stunting in a conflict-ridden border region in Armenia - a cross-sectional study
https://doi.org/10.1186/s40795-017-0204-9
© The Author(s). 2017
Received: 13 March 2017
Accepted: 16 November 2017
Published: 2 December 2017
Abstract
Background
Despite global efforts, stunting remains a public health problem in several developing countries. The prevalence of stunting among 0- to 5-year-old children in Armenia has increased from 17% in 2000 to 19% in 2010. A baseline study was conducted among preschool children in Berd, a region near the northeastern border of Armenia that has experienced intermittent military tension for over 20 years.
Methods
We conducted a cross-sectional study including 594 children aged 6-month- 6 years old and their caregivers in our analysis, to assess the prevalence and determinants of stunting. We calculated the anthropometric measurements and hemoglobin levels of children; analyzed children’s stool and conducted a survey with children’s caregivers. We employed the hierarchical logistic regression model to explore the predictors of stunting among 25–72 months old children and multivariable logistic regression models to investigate the predictors of stunting among 6–24 months old children. Individual and residence level variables were included in the models including anemia, minimum dietary diversity, mothers’ height, the overall duration of breastfeeding, birthweight, child’s history of diarrhea and mean socio-economic score.
Results
The prevalence of stunting was significantly higher among the 6–24 months old children (13.3%) compared to the children aged 25–72 months old (7.8%). We did not find any differences in the prevalence of stunting by place of residence in either age group. The 6–24 months old children who consumed at least four food groups during the previous day (minimum dietary diversity) had 72% lower odds of being stunted (p < 0.05). Each kilogram increase in birthweight was associated with 76% lower odds of being stunted (OR = 0.24, p < 0.01). Mother’s height significantly decreased the odds of stunting among the children 25–72- months old (OR = 0.86, p < 0.001). BMI was also a significant predictor of stunting among both age-groups.
Conclusions
The study results highlight the significance of mother’s height, birthweight, and adequate complementary feeding to reduce stunting. Further studies are needed to determine the possible association of anemia and stunting with the ongoing conflict in the region, as well as socioeconomic conditions and food insecurity in the region.
Keywords
Background
Several studies have found that protracted conflicts have an adverse impact on health [1–3]. Current on-going conflicts in the former Soviet states, such as Ukraine, and in the nearby Middle East certainly have an impact on childhood health [4, 5]. Armenia is one such conflict-ridden former Soviet country, located in the Caucasus region. Long-standing military tensions may exacerbate health and nutrition status of vulnerable populations affected by such circumstances, particularly young children [6].
According to the World Health Organization (WHO), 54% of all child deaths are associated with undernutrition [7]. Despite global efforts to achieve the Millennium Development Goals, the percentage of stunted children under age five remains high. Since 1990, there has been a steady decrease in stunting worldwide; however, it is estimated that globally in 2016, 24% of children under age five were still stunted [8, 9]. Stunting during childhood can lead to reduced immunity, increased susceptibility to non-communicable diseases, impaired physical and mental development, and reduced productivity [10].
Several factors influence stunting, including the socioeconomic status of the household, parents’ education, anemia, soil-transmitted helminths (STH) infections, diarrheal infections, dietary intake and complementary feeding [11–22]. Short overall duration of breastfeeding, as well as the late introduction of appropriate solid foods, have both been associated with stunting in many studies [18, 23–26] Birth outcomes such as low birth weight and birth length are also important factors that are associated with higher prevalence of stunting [24, 27, 28].
In a study conducted in Sri Lanka, maternal height was inversely related to the prevalence of stunting [18]. Low birthweight was associated with higher rates of stunting in the same study. Socioeconomic status of the family was associated with stunting in among school children in Nigeria [29]. In another study conducted in Nigeria, children who did not receive timely complementary feeding and children with less than minimum food diversity had higher odds of being stunted. [22].
There are limited data regarding infant and child nutrition status in the Republic of Armenia. The Armenian Demographic and Health Survey (ADHS), conducted every 5 years, is the primary source of information regarding nutrition and child growth patterns. According to the 2010 ADHS, the prevalence of stunting among 0- to 5-year-old children increased to 19% from 17% in 2000 [16]. A recent study conducted in Yerevan, the capital of Armenia, identified the prevalence of stunting as 17.9% among 5- to 17-month-old children, which is close to the 2010 ADHS estimated percentage of around 17.3% in Yerevan [16, 30].
According to the ADHS, the prevalence of stunting in 2010 was 16.1% in the Tavush province [16] which was one of the regions with the highest prevalence of stunting in Armenia. Frequent tensions and skirmishes along the Armenian–Azerbaijani border have increased in recent years [31–33], resulting in diminished agricultural capacity and affecting socioeconomic conditions in this region. Tensions are intense in the Berd region in particular, because of its proximity to the border between Armenia and Azerbaijan.
The growing trend of stunting in Armenia necessitates a thorough investigation to understand its risk factors to inform policies and interventions to reverse the trend. Although the determinants of stunting have been well investigated in several studies, the specific precursors of stunting might vary among different countries and regions [34]. This different pattern is evident among former Soviet countries [30, 35]. Therefore, it is important to study the risk factors responsible for nutritional problems of children specific to Berd region in Armenia.
The main aim of this study was to determine the prevalence and determinants of stunting among preschool children in Berd city and its seven surrounding rural communities, a vulnerable border region in the Tavush province in the Republic of Armenia, which is itself a low-middle income country. We specifically explored if there are significant differences in the prevalence of stunting among the children 6–24 months and 25–72 months old. We also examined if the prevalence of stunting in each age group was different by place of residence. We further investigated the influence of anemia, soil-transmitted helminths, feeding practices, dietary intake, maternal and household characteristics and birth outcomes on stunting among children 6–24 months and 25–72 months old.
Methods
Study design
This cross-sectional study included anthropometric (height, weight) measurements, blood tests to measure hemoglobin (HgB) levels of 6-month to 6-year-old children, and stool analysis for intestinal STH in 12-months to 6-year-old children. The survey also included a questionnaire for caregivers (mainly mothers) to understand the determinants of malnutrition in the target communities. The study was designed and conducted from September 2013 to March 2014.
Study population
The study population for the anemia analysis and anthropometric measurements included all 6-month to 6 year-old children living in the city of Berd and seven surrounding rural communities (Chinchin, Varagavan, Paravakar, Verin Caghkavan, Nerkin Karmiraghbyur, Tavush, and Aygepar). The only exclusion criteria were if the child was diagnosed with a blood coagulation or neurological disease; however, no child in our sample met the exclusion criteria.
Population size and sampling method
A representative sample of children from Berd city aged 6 months to 6 years old was randomly selected to participate in the study (n = 352). Study participants were chosen from a sample frame consisting of all children living in Berd city, as registered in the Tavush province’s administrative records. The children from Berd were selected based on a stratified random sampling strategy. We chose age groups (year) as the strata. The number of the samples within each age group (stratum) were calculated separately based on \( \mathrm{n}=\frac{{\mathrm{Z}}^2\mathrm{P}\left(1\hbox{-} \mathrm{P}\right)}{{\mathrm{d}}^2} \) equation to estimate population prevalence [36, 37]. Since the total number of children in the rural communities was small, the study team included all children and caregivers from these areas (n = 491).
Data collection
Healthcare providers in rural and urban primary healthcare facilities (family physicians and laboratory physicians and nurses) were trained in the study protocols and assigned as study coordinators in their regions. The adherence to study protocols by coordinators and staff was monitored through frequent spot-checks. The anthropometric measurements, blood and stool analysis, and surveys with the parents/caregivers took place in the primary healthcare facilities in Berd and the local rural communities. The study coordinators obtained a written informed consent from the caregivers of all participants. After collecting the child’s anthropometric measurements, the caregiver participated in a survey administered by the physician or nurse. The survey questionnaire included questions about maternal and child characteristics, infant feeding practices, birth outcomes and child’s dietary intake, measured by 24-h recall.
Measurements
The HgB levels of the children were measured using HemoCue® HB 301, a U.S. Food and Drug Administration (FDA)-approved device designed for quick analysis of HgB in capillary, venous, or arterial blood [38–41]. As recommended by the WHO for STH surveys, we conducted stool tests on samples from 12-months to 6-year-old children from the Berd region [42].
The Kato-Katz method was used to perform the stool analyses [42]. This technique is utilized to diagnose STH, such as Ascaris lumbricoides, and Trichuris trichiura, in stool samples [43]. We provided stool container kits to parents to collect the stool samples. Parents were instructed to collect the first morning stool of their children. They were also instructed to refrigerate the stool samples and transport them to the nearest local healthcare facility within 12 h of collection.
We adapted the WHO, and UNICEF Infant and Young Child Feeding (IYCF) practices questionnaire to assess feeding practices as well as maternal and child characteristics in the target region [42, 44]. These questions were translated and validated for use in the ADHS 2010 [16]. We made minor changes to the questionnaire to gain information on maternal education, in addition to the history of soil-transmitted helminths disease, anemia, and diarrhea. The primary health care physicians administered the after the anthropometric measurements, and blood samples were collected by the nurses.
Children’s weight was measured using electronic scales. The children’s height (length in recumbent status for children younger than 24 months) was measured with appropriate measuring boards or stadiometers by the trained primary health care providers in the study sites.
Study variables
The primary outcome variable was stunting, analyzed as a dichotomous outcome. Stunting was considered positive for all the children whose height-for-age was below -2SD compared to the median height-for-age of the WHO growth standards [45].
Anemia, one of the explanatory variables, was considered positive for the children with blood HgB levels lower than 110 g/L. Altitude adjustments were made to the HgB values of the children living in areas more than 1000 m above sea level [46]. The presence of STH confirmed via stool laboratory analysis was another explanatory variable.
The survey questionnaire administered to caregivers asked about child’s birth weight and birth length; child’s age; any breastfeeding; exclusive breastfeeding; breastfeeding duration; residence; mother’s height; mother’s participation in community training about child nutrition; accessibility of printed materials about child nutrition; any history of prolonged diarrhea or STH reported by the caregiver; and a detailed dietary intake assessment of the child during the last 24 h.
We used a standardized socio-economic score as a composite of (a)mothers’ education; (b) the financial status of the family compared to neighboring households; (c)food insecurity. Further, we calculated the mean socioeconomic status score based on the place of residence. The information about birth weight, birth length and birthdate were confirmed based on administrative records.
To assess the effect of conflict on stunting, we created a variable based on the geographical distance from the border and front lines of the conflict zone. The two villages closest to the front line were considered positive for being exposed to violence.
Minimum dietary diversity, another explanatory variable, was created based on the scoring system of the WHO and UNICEF indicators [44] for the assessment of infant and young child feeding practices. It included seven food groups (grains, legumes, dairy, flesh, eggs, Vitamin A-rich foods, and other fruits and vegetables). Children who had consumed at least four of the seven groups were scored as positive. Children whose birthweight were less than 2500 g were considered having a low birthweight as suggested by WHO and UNICEF [43].
Data management and statistical analysis
The data were double entered using SPSS 21.0 and analyzed using SAS 9.4 statistical software. We calculated frequencies and proportions to describe categorical variables and computed means and standard deviations for continuous variables. We used Chi-Square and ANOVA to assess the intergroup comparison for children 6–24 months and 25–72 months old separately. We further examined whether the association between stunting and main predictor variables was modified by place of residence using Breslow-Day test.
Univariable Logistic Regression Analysis Results for the association between explanatory variables and stunting
Variable Name | 6–24-months old children | 25–72-months old children | ||
|---|---|---|---|---|
OR | 95% CI | OR | 95% CI | |
Birth weight (kilograms) | 0.47 | [0.20–1.08] | 0.61 | [0.31–1.22] |
Low birthweight (<2500 g) [Yes/No(Ref)] | 2.06 | [0.52–8.19] | 1.88 | [0.62–5.74] |
Birth length (centimeters) | 0.88 | [0.76–1.02] | 0.96 | [0.80–1.15] |
Body mass Index | 1.31* | [1.06, 1.62] | 1.16* | [1.01, 1.34] |
Breastfeeding duration (months) | 1.06 | [0.98–1.15] | 1.05* | [1.00–1.10] |
Child’s history of diarrhea [Yes/No(Ref)]a | 3.21* | [1.15–8.95] | 1.42 | [0.52–3.86] |
Caregiver’s participation in community training programs [Yes/No(Ref)] | 0.56 | [0.12–2.60] | 0.39 | [0.12–1.32] |
Child’s gender [male/female(ref)] | 0.86 | [0.35–2.14] | 2.42* | [1.1–5.31] |
Child’s age (months) | 1.10* | [1.01–1.20] | 0.99 | [0.96–1.01] |
Mother’s height (cm) | 0.91* | [0.84–0.99] | 0.89** | [0.84–0.96] |
Anemia [Yes/No(Ref)] b | 0.48 | [0.18–1.29] | 1.93 | [0.75, 4.95] |
Minimum dietary diversity [Yes or No(Ref)] c | 0.45 | [0.18–1.11] | 0.78 | [0.37–1.65] |
Exclusive breastfeeding reported by mother [Yes/No(Ref)] d | 1.13 | [0.45–2.80] | 0.89 | [0.38–2.13] |
Composite standardized SES score e | 0.82 | [0.52–1.29] | 1.53 | [0.85, 2.74] |
Child’s history of iron medication intake [Yes/No(Ref)] | 2.27 | [0.43–12.01] | 1.12 | [0.25–5.01] |
Child’s previous history of soil-transmitted helminth disease [Yes/No(Ref)] | <0.001 | [0–999.99] | 0.94 | [0.40–2.23] |
Soil-transmitted helminth (lab analysis) | 1.51 | [0.46–5.0] | 1.34 | [0.61–2.91] |
Negative (ref) | 1.00 | 1.00 | ||
Ascaris lumbricoides | 2.27 | [0.56, 9.23] | 0.93 | [0.27,3.26] |
Trichuris trichiura (whipworm) | 0.85 | [0.10, 7.24] | 1.80 | [0.73, 4.42] |
hookworms | – | <0.001 | [0–999.99] | |
pinworms | <0.001 | [0–999.99] | <0.001 | [0–999.99] |
Residence [urban/rural(Ref)] | 1.14 | [0.46–2.85] | 1.51 | [0.74–3.11] |
Financial condition of the family compared to neighbors f | ||||
Significantly below average (Ref) | 1.00 | 1.00 | ||
Below average | 0.83 | [0.22, 3.14] | 1.34 | [0.31, 5.85] |
Average | 0.42 | [0.13, 2.41] | 1.94 | [0.56, 6.72] |
Above average | 0.26 | [0.03,2.46] | 2.62 | [0.49, 13.91] |
Significantly above average | 0.45 | [0.04, 4.5] | 4.2 | [0.62, 28.35] |
Maternal Education | ||||
> highschool (10 years) (Ref) | 1.00 | 1.00 | ||
≤ highschool (10 years) | 1.22 | [0.49, 3.01] | 0.87 | [0.42, 1.83] |
To build our final models, we first explored the association between the dependent and independent variables using binary logistic regression for both age groups using the LOGISTIC procedure in SAS. We further fitted the data for each age group separately conducting multilevel logistic regression analysis by proc. glimmix procedure in SAS, assuming the place of residence as the group variable and the highest level of the hierarchy.
The estimated G matrix was not positive definite for the unconditional model estimating predictors of stunting among children 6–24 months old. Therefore, we used the multivariable logistic regression model to estimate the predictors of stunting among children in this age group.
To estimate the predictors of stunting for the children 25–72 months old, we used the multilevel logistic regression approach. Utilizing the Likelihood ratio test (LRT) and Akaike’s Information Criterion (AIC) we compared the hierarchical models to estimate the predictors of stunting among 25–72 months old children and to examine the improvement in model fit.
Model A was the multivariable logistic regression model including all the individual level predictors adjusted by age and gender of the child. Model B was the multilevel logistic regression model assuming variance components (VC) G matrix for all the residence groups and including only the random intercept to estimate the effect of a typical residence place level effect. In model C, we included only the individual level variables to account for the crude effects of these variables in the presence of random intercept. Model D included anemia as another individual level predictor. Subsequently, we included the residence-level mean socio-economic composite score variable in model E to explain the residence level variation in stunting. However, we did not observe a significant association between stunting and the residence level mean socio-economic composite score, and the inclusion of the variable did not improve the model fit. Model F included all the variables in model D, adjusted for age and gender. Finally, model G included all the variables in model E, adjusted for age and gender. We refrained from including random slope since it did not significantly improve the model fit when comparing to model F using LRT test.
The multivariable logistic regression models to estimate the predictors of stunting among 6–24 months old children were tested and compared by the Hosmer–Lemeshow goodness-of-fit test, AIC and LRT and Nagelkerke’s R2. The multivariable logistic regression analysis resulted in six consecutive models. The final model included all the statistically and clinically significant variables that had the highest Hosmer–Lemeshow test score and pseudo R2 to predict the prevalence of stunting. Model A includes crude unadjusted predictors of stunting including birthweight, child’s history of any diarrhea reported by the caregiver, and minimum dietary diversity. Model B included all the individual level variables in model A adjusting for age of the child by months and gender of the child. We included anemia, standardized socio-economic score, and presence of soil-transmitted helminth infection in each of the three consecutive models subsequently. However, including the variables did not contribute to the model fit.
Results
Demographic and baseline characteristics of study participants overall and by age group
Child’s age | |||||
|---|---|---|---|---|---|
Categories | Total (N = 604) | 6–24 months old | 25–72 months old | p valuea | |
Demographic characteristics | |||||
Gender, n (%)* | |||||
Male | 323 (53.48) | 81 (48.79) | 242 (55.25) | 0.15 | |
Female | 281 (46.52) | 85 (51.20) | 196 (44.75) | ||
Location, n (%) | |||||
Berd | 208 (34.43) | 63 (37.95) | 145 (33.11) | 0.26 | |
Rural Areas | 396 (65.57) | 103 (62.05) | 293 (66.89) | ||
Baseline characteristics | |||||
Birthweight, mean (SD), Kilograms | 3.15 (0.50) | 3.14 (0.52) | 3.16 (0.50) | 0.67 | |
Birthlength, mean (SD), centimeters | 49.74 (2.24) | 49.57 (2.64) | 49.80(2.07) | 0.27 | |
Breastfeeding duration, mean (SD), months | 11.46 (7.16) | 9.92 (5.67) | 12.04 (7.58) | 0.00 | |
Mother’s height, mean(SD), centimeters | 159.46 (5.84) | 159.83 (5.78) | 159.33(5.87) | 0.35 | |
Composite SES score, mean (SD) | 8.88 (1.60) | 8.99(1.73) | 8.83(1.55) | 0.30 | |
Body Mass Index, mean (SD) | 16.72 (2.22) | 17.73 (2.17) | 16.34 (2.12) | 0.00 | |
Maternal Education, n (%) | |||||
≤ highschool (10 years) | 370 (61.26) | 98 (59.04) | 272 (62.1) | 0.49 | |
> highschool (10 years) | 234 (38.74) | 68 (40.96) | 166 (37.9) | ||
Financial condition of the family compared to neighbors | |||||
Significantly below average | 89 (14.74) | 23 (13.86) | 66 (15.07) | 0.22 | |
Below average | 115(19.04) | 32 (19.28) | 83 (18.95) | ||
Average | 336 (55.63) | 86 (51.81) | 250 (57.08) | ||
Above average | 42 (6.95) | 15 (9.04) | 27 (6.16) | ||
Significantly above average | 22 (3.64) | 10 (6.02) | 12 (2.74) | ||
Child’s history of diarrhea, n (%) | |||||
Yes | 73 (12.2) | 25(15.15) | 48 (11.09) | 0.17 | |
No | 525 (87.8) | 140 (84.85) | 385 (88.91) | ||
Caregiver’s participation in community training programs, n (%) | |||||
Yes | 107 (18.20) | 23 (14.11) | 84 (19.27) | 0.22 | |
No | 490 (81.80) | 140 (85.89) | 350 (80.28) | ||
Exclusive breastfeeding reported by mother, n (%) | |||||
Yes | 199 (39.10) | 90 (56.25) | 220 (63.04) | 0.14 | |
No | 310 (60.90) | 70 (43.75) | 129 (36.96) | ||
Child’s history of sleeping hungry reported by caregiver, n (%) | |||||
Always | 3 (0.50) | 0 | 3 (0.69) | 0.55 b | |
Often | 10 (1.68) | 4 (2.44) | 6 (1.38) | ||
Sometimes | 69 (11.56) | 21 (12.80) | 48 (11.09) | ||
Never | 515 (86.26) | 139 (84.76) | 376 (86.84) | ||
Child’s history of iron medication intake, n (%) | |||||
Positive | 31 (5.16) | 8 (4.85) | 23 (5.52) | 0.80 | |
Negative | 568 (94.84) | 157 (95.15) | 411(94.48) | ||
Child’s previous history of soil-transmitted helminth disease, n (%) | |||||
Positive | 97 (16.19) | 4 (2.42) | 93 (21.43) | 0.00 | |
Negative | 502 (83.81) | 161 (97.58) | 341 (78.57) | ||
Minimum Dietary Diversity, n (%) | |||||
Positive | 414 (68.54) | 97 (58.43) | 317 (72.37) | 0.00 | |
Negative | 190 (31.46) | 69 (41.57) | 121 (27.63) | ||
Soil-transmitted helminth confirmed by Kato Katz method, n (%) | |||||
Negative | 469 (78.69) | 142 (86.59) | 327 (75.58) | 0.49 c | |
Ascaris lumbricoides | 57 (9.56) | 12 (7.32) | 45 (10.37) | ||
Trichuris trichiura (whipworm) | 67 (11.25) | 9 (5.49) | 58 (13.59) | ||
hookworms | 1 (0.17) | 0 | 1(0.23) | ||
pinworms | 2 (0.33) | 1(0.61) | 1 (0.23) | ||
Stunting, n (%) | |||||
Positive | 56 (9.32) | 22 (13.33) | 34 (7.80) | 0.03 | |
Negative | 545 (90.68) | 143 (86.67) | 402 (92.20) | ||
Anemia, n (%) | |||||
Positive | 115 (19.07) | 69 (41.57) | 46 (10.53) | 0.00 | |
Negative | 488 (80.93) | 97 (58.43) | 391 (89.47) | ||
Demographic and baseline characteristics of study participants overall and by age group stratified by place of residence
Child’s age | |||||||||
|---|---|---|---|---|---|---|---|---|---|
Categories | Total (N = 604) | Urban (N = 208) | Rural (N = 396) | p valuea | |||||
6–24- month old | 25–72 month old | OR | 6–24- month old | 25–72 month old | OR | ||||
Stunting, n (%) | |||||||||
Positive | 56 (9.32) | 9 (14.28) | 14 (9.67) | 1.56 | 13 (12.75) | 20 (6.87) | 1.98 | 0.68 | |
Negative | 545 (90.68) | 54 (85.72) | 131 (90.33) | 89 (87.25) | 271 (93.13) | ||||
Anemia, n (%) | |||||||||
Positive | 115 (19.07) | 20 (31.75) | 13 (8.97) | 4.72*** | 49 (47.57) | 33 (11.30) | 7.12*** | 0.73 | |
Negative | 488 (80.93) | 43 (68.25) | 132 (91.03) | 54 (52.43) | 259 (88.70) | ||||
Minimum Dietary Diversity, n (%) | |||||||||
Positive | 414 (68.54) | 43 (68.25) | 112 (77.24) | 1.58 | 54 (52.43) | 205 (69.97) | 2.11** | 0.50 | |
Negative | 190 (31.46) | 20 (31.75) | 33 (22.76) | 49 (47.57) | 88(30.03) | ||||
Soil-transmitted helminth confirmed by Kato Katz method, n (%) | |||||||||
Positive | 130 (21.70) | 3 (1.44) | 26 (17.93) | 0.22** | 19 (18.81) | 82 (28.28) | 0.59 | 0.16 | |
Negative | 469 (78.30) | 60 (95.24) | 119 (82.07) | 82 (81.19) | 208 (71.72) | ||||
Low Birthweight n (%) (Birthweight < 2500 g) | |||||||||
Yes | 45 (7.58) | 3 (4.84) | 7 (4.83) | 1.00 | 10 (9.80) | 25 (8.77) | 1.13 | 0.88 | |
No | 549 (92.42) | 59 (95.16) | 138 (95.17) | 92 (90.20) | 260 (91.23) | ||||
Estimated predictors of Stunting among 6–24- month old Children
Model A | Model B | Model C | Model D | Model E | |
|---|---|---|---|---|---|
OR (95%CI) | OR (95%CI) | OR (95%CI) | OR (95%CI) | OR (95%CI) | |
Effects Estimates | |||||
Gender | |||||
Male | 0.82 (0.28, 2.42) | 0.81 (0.27, 2.4) | 0.80 (0.39, 2.95) | 0.82 (0.28, 2.41) | |
Female (Ref) | 1.00 | 1.00 | 1.00 | 1.00 | |
Age | 1.25 ** (1.11, 1.41) | 1.25***(1.10, 1.41) | 1.25*** (1.10, 1.41) | 1.24*** (1.10, 1.40) | |
BMI | 1.30* (1.05, 1.63) | 1.55*** (1.2, 2.01) | 1.55***(1.20, 2.01) | ||
Birthweight, Kilograms | 0.40 (0.16, 1.03) | 0.24** (0.08, 0.71) | 0.26* (0.08, 0.80) | 0.20** (0.06, 0.62) | 0.24** (0.08, 0.70) |
Child’s history of diarrhea | |||||
Yes | 3.85* (1.27, 11.69) | 2.83 (0.83, 9.66) | 2.88 (0.84, 9.86) | 2.56 (0.73, 8.92) | 2.93 (0.85, 10.07) |
No (Ref) | 1.00 | 1.00 | 1.00 | 1.00 | 1.00 |
Minimum Dietary Diversity | |||||
Positive | 0.58 (0.22, 1.55) | 0.28* (0.09, 0.87) | 0.29* (0.09, 0.91) | 0.27* (0.09, 0.88) | 0.28 * (0.09, 0.87) |
Negative (Ref) | 1.00 | 1.00 | 1.00 | 1.00 | 1.00 |
Standardized socioeconomic status score | 0.87 (0.50, 1.51) | ||||
Anemia | |||||
Positive | 0.34 (0.10, 1.12) | ||||
Negative(Ref) | 1.00 | ||||
Soil-transmitted helminth confirmed by Kato Katz method, n (%) | |||||
Positive | 1.36 (0.34, 5.45) | ||||
Negative (Ref) | 1.00 | ||||
Model goodness of fit | |||||
-2logL | 111.801 | 95.708 | 95.391 | 92.274 | 95.524 |
AIC | 121.801 | 109.708 | 111.391 | 108.274 | 111.524 |
Hosmer Lemeshow test | 0.84 | 0.79 | 0.81 | 0.43 | 0.53 |
Also in model B, each kilogram increase in birth weight was associated with 76% lower odds of being stunted (OR = 0.24, p < 0.01). BMI also appeared to be a significant predictor of stunting in model B. The odds of stunting increased by 55% with each unit increase in BMI score (OR = 1.55 p < 001). Finally, with each increasing month of age, the children had higher odds of being stunted (OR = 1.25, p < 0.001). Therefore, significant predictors of stunting in children age 6–24 months were minimum dietary diversity, birthweight, BMI, and age.
Estimated predictors of Stunting among 25–72- month old Children
Model A | Model B | Model C | Model D | Model E | Model F | Model G | |
|---|---|---|---|---|---|---|---|
OR (95%CI) | OR (95%CI) | OR (95%CI) | OR (95%CI) | OR (95%CI) | OR (95%CI) | OR (95%CI) | |
Fixed Effects Estimates | |||||||
Gender | |||||||
Male | 2.36* (1.03,5.38) | 2.5* (1.05, 5.9) | 2.47* (1.04,5.86) | ||||
Female (Ref) | 1.00 | 1.00 | |||||
BMI | 1.22* (1.04, 1.42) | 1.25**(1.07, 1.47) | 1.25**(1.07, 1.47) | 1.26** (1.07, 1.48) | 1.26** (1.06, 1.49) | 1.26** (1.06, 1.5) | |
Age | 0.98 (0.96, 1.01) | 0.99 (0.96, 1.01) | 0.99 (0.96, 1.01) | ||||
Breastfeeding duration (months) | 1.05* (1.00, 1.10) | 1.06* (1.00, 1.10) | 1.05* (1.00, 1.11) | 1.05* (1.00, 1.11) | 1.04 (0.99, 1.10) | 1.04 (0.99, 1.1) | |
Mother’s height (centimeters) | 0.87*** (0.81, 0.94) | 0.87 *** (0.81, 0.94) | 0.86 *** (0.80, 0.94) | 0.87*** (0.81,0.94) | 0.87***(0.81,0.94) | 0.86***(0.79,0.93) | |
Anemia | |||||||
Positive | 2.28(0.79, 6.61) | 2.39 (0.82, 6.94) | 2.19 (0.75, 6.39) | 2.30 (0.79, 6.72) | |||
Negative(Ref) | 1.00 | 1.00 | 1.00 | 1.00 | |||
Residence level variables | |||||||
Mean Socioeconomic score | 2.06 (0.70, 6.1) | 2.13 (0.67, 6.7) | |||||
Error Variance | |||||||
Residence Level Intercept (SE) | 0.47 (0.51) | 0.54 (0.57) | 0.50 (0.53) | 0.45 (0.50) | 0.54 (0.56) | 0.39 (0.48) | |
Model goodness of fit | |||||||
-2logL | 202.571 | 235.75 | 204.69 | 202.59 | 199.97 | 197.34 | 194.79 |
AIC | 214.571 | 239.75 | 214.69 | 214.59 | 213.97 | 213.34 | 212.79 |
ICC | 0.12 | 0.14 | 0.13 | 0.12 | 0.11 | 0.13 | |
Discussion
Our study found that the prevalence of stunting was higher among children 6–24 months old in both Berd and the rural areas compared to children aged 25–72 months old in the same region. The higher proportion of stunting and anemia among children 6- to 24-months old might be related to recent increases in border conflict in this area (Table 3). The lower prevalence of stunting in children 25–72 months old could be explained by the catch-up growth phenomenon [48, 49].
We found that minimum dietary diversity was significantly and negatively associated with stunting among children 6–24 months old. These findings strengthen the argument that factors such as inadequate complementary feeding and low minimum dietary diversity might be the most critical areas to address in public health interventions to decrease the prevalence of stunting, particularly among children aged 6 to 24 months. Moreover, the preventive effect of minimum dietary diversity on stunting (see Tables 4 and 5) is similar to other studies conducted in the Republic of Armenia and other countries [30, 50, 51].
We also found that the higher the birth weight (analyzed as a continuous variable), the lower the odds of stunting among 6–24 months -old children, which is consistent with the literature [11, 52–54]. Nevertheless, there was not a statistically significant association between low birth weight (dichotomous) and stunting in the final multivariable model, as is often seen in the literature [18, 24, 28]. This could be because the prevalence of low birth weight in this age group was low (9.8% [95%CI 3.9, 15.6] in rural areas and 4.8% [95%CI 0.6, 10.3] in Berd). Our findings suggest that analyzing birthweight as a continuous variable might be more appropriate.
The association between BMI and stunting among children was one of the novel findings of our study. We found that the odds of stunting increased significantly among children in both age-groups with each unit increase in BMI adjusting for other predictors in our models (Tables 4 and 5). This finding could indicate that stunting and overweight can be experienced in the same individuals. In fact, the double burden of malnutrition is a rising problem in low and middle-income countries. [55]. Although we could not establish the sequential events in the development of stunting and BMI trajectories in our study population, it is hypothesized that stunted children are more predisposed to become overweight. This association has already been explored in several studies [56–59]. This phenomenon is also explained by dietary consumption patterns which are poor in animal protein and high in carbohydrates and fats [57]. We found that minimum dietary diversity was lower among 6–24- month old children. This finding could explain the significant association of BMI with stunting in our study population.
We found that, with each centimeter increase in the mother’s height, the odds of stunting among all children aged 25–72 months old decreased by 13%. This finding, which is consistent with the literature, indicates the possible role of genetics and the intergenerational effect of malnutrition on the development of stunting [18, 60].
We also found that the odds of stunting among boys were 2.36 times the odds of stunting among girls in the 25–72 months old. Several studies conducted predominantly in Sub-Saharan Africa have found similar results [61–63]. This finding could be explained by the higher vulnerability of male children towards early life adversities in comparison with females [63–65]. Particularly, boys were more likely to need advanced life support than girls in a study conducted among preterm and low-birthweight children [64]. In another study conducted among the low-birthweight infants, girls were more likely to survive to 5 years of age than the males [65].
The overall prevalence of anemia was high in our study population. However, anemia was not significantly associated with stunting in univariable and multivariable models among any of the age groups. The prevalence of anemia was significantly higher among the 6–24 months old children compared to 25–72 months old children in both the rural and urban areas. A possible explanation for this finding could be the lower dietary diversity among 6–24 months old children compared to children aged 25–72 months (Table 3).
A history of long episodes of diarrhea was only associated with stunting among the 6–24 months old children in the multivariable logistic regression. However, the association faded away after adjusting for age and gender and in hierarchical models. In fact, diarrhea was found to be associated with stunting in similar studies [66–69]. During episodes of diarrhea, children lose water and micronutrients, which can result in malnutrition if not adequately replaced. We recognize that this variable was subjective and “long episodes of diarrhea” was not well defined for the survey respondents. This finding, nonetheless, suggests that history of diarrhea may be a significant predictor of stunting among 6–24 months old children, and better measurements of the history of diarrhea in future studies could further explore this relationship.
The positive effect of overall duration of breastfeeding (months) on the development of stunting among 25–72 months old children, although very small (OR = 1.05), may indicate inadequate complementary feeding, which is also supported by the finding of low minimum dietary diversity. It could also indicate the inadequate frequency of breastfeeding during the day; however, the frequency of breastfeeding was not measured in this study.
This is the first study in this restive border region assessing the trends and determinants of stunting. The study included the entire community in the rural areas (census), which indicates that the statistical inferences were accurate for the rural regions and the representative random sample from the Berd region also increases the generalizability of the results. The authors pretested the questionnaire along with study coordinators in the region to minimize the possibility of measurement errors.
Nevertheless, there were several limitations in this study. The questionnaire utilized for the survey with mothers lacked questions regarding the water and sanitation situation of the respondents’ households. Although our instrument assessed the diet of the children based on 24-h recall questions, we do not exclude the possibility of recall bias. Recall bias may also have affected responses to other subjective questions like those related to diarrhea and breastfeeding duration. The stool analysis was also only conducted once and not in a modern laboratory. However, this misclassification would be non-differential. We also did not include a separate question to assess the frequency and level of border conflict in each study site in our survey. We did not find a significant association between residence-level mean socioeconomic score and stunting in our hierarchical models. We acknowledge that our questionnaire did not capture accurate information to calculate the socio-economic score for individuals. Only three variables were measuring the socioeconomic status of the study participants’ households. Furthermore, our questionnaire did not assess the family income and father’s occupation accurately, which could help us to determine the family’s socio-economic position better.
Conclusions
This study identified several risk factors that are associated with the development of stunting among children in the conflict-ridden border regions of Armenia. Factors such as minimum dietary diversity and history of previous episodes of diarrhea indicate the necessity of adequately feeding children as well as the management of the diarrheal disease. The findings of this study will contribute to the development of appropriate interventions targeting timely complementary feeding in vulnerable regions to reduce stunting. Although anemia was not associated with stunting, the prevalence of anemia was very high among the 6–24 months old children and should be a focus of dietary intake interventions to promote optimal growth patterns among children in the region. Further research should consider a more thorough questionnaire to capture the socioeconomic status of the study participants, to determine the association between anemia and stunting, and to further assess the effect of the ongoing conflict in the region. The findings of this study can inform public health programmers and policymakers to focus on promoting appropriate complementary feeding, dietary diversity, and management of diarrhea for optimal growth among young children in this region.
Abbreviations
- ADHS:
-
Armenian Demographic and Health Survey
- AIC:
-
Akaike’s Information Criterion
- CI:
-
Confidence Interval
- FDA:
-
United States Food and Drug Administration
- HgB:
-
Hemoglobin
- ICC:
-
Intraclass Correlation Coefficient
- LRT:
-
Likelihood ratio test
- SD:
-
Standard Deviation
- STH:
-
Soil-transmitted Helminths
- VC:
-
Variance Components
- WHO:
-
World Health Organization
Declarations
Acknowledgements
Authors acknowledge Fund for Armenian Relief and Edward and Helen Mardigian Foundation for sponsoring and providing facilities to conduct this study. Authors also acknowledge Susanna Ayvazyan MD, Gohar Babayan MD, Asia Mardanyan MD, Alina Araqelyan MD and Gayane Gevorgyan MD for coordinating the data collection in the Berd region.
Funding
The study was financed by Fund for Armenian Relief as a baseline assessment for “Breaking Cycle of Poverty in Berd Region-Tavush, Armenia” program.
Authors’ information
AB was the healthcare and social programs officer at the time the study was conducted; AB is currently a doctoral candidate in Department of Epidemiology in Mailman School of Public Health at the Columbia University. RD is the Robert R. Williams Professor and the Director of Institute of Human Nutrition, and Professor of Departments of Pediatrics and Epidemiology at Columbia University. HS is the Director of Healthcare programs and AS is the healthcare and social programs officer at Fund for Armenian Relief of America. KH is an Assistant Professor of the Institute of Human Nutrition at Columbia University.
Availability of data and materials
The Berd Children coded data that support the findings of this study are available in Zanodo digital repository (DOI: https://doi.org/10.5281/zenodo.51704).
Authors’ contributions
AB designed the study, managed data collection and analysis of collected data, HS designed the study, managed data collection, participated in manuscript drafting. KH participated in data analysis and drafted the manuscripts. RD participated in the analysis of data and drafting the manuscript. AS participated in the analysis of data and drafting the manuscript. All authors read and approved the final manuscript.
Ethics approval
The study was conducted according to the declaration of Helsinki and all the procedures involving human subjects were approved by the Institutional Review Board of the American University of Armenia (AUA-2013-014). Written informed consent was obtained from the caregivers of all participants.
Consent for publication
Not applicable.
Competing interests
The financial resources for this study were provided by the Fund for Armenian Relief. HS and AS are employees of the Fund for Armenian Relief; AB was an employee of Fund for Armenian Relief. KH and RD declare no conflict of Interest.
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Authors’ Affiliations
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