Abstract
Objective
To evaluate the association between weight gain in the first two years of life and the occurrence of wheezing, asthma, serum IgE, skin reactivity and pulmonary function.
Design
Cohort study.
Setting
The metropolitan region of Salvador, Bahia, Brazil.
Subjects
The association was studied between 1997 and 2005 in 669 children up to 11 years of age. Data were collected on asthma and risk factors, both current factors and those present in the first years of life. Weight gain was considered fast when the Z-score was >0·67. Poisson regression was used in the multivariate statistical analysis.
Results
Wheezing was reported in 25·6 % of the children. Weight gain was considered fast (Z-score >0·67) in 29·6 % of the children and slow (Z-score <−0·67) in 13·9 %. Children in the slow weight gain group had 36 % fewer symptoms of asthma (prevalence ratio = 0·65; 95 % CI 0·42, 0·99).
Conclusions
Slower weight gain in the early years of life may constitute a protective factor against symptoms of asthma. The relevance of this finding for public health is not yet certain, since it is known that children with slow and fast weight gain may be more likely to develop adverse health consequences related to both these situations.
Keywords: Weight gain, Children, Asthma, Atopy, Pulmonary function
Fast weight gain in the first year of life has been suggested to be a potential risk factor for the occurrence of obesity and chronic diseases in childhood( 1 ) and adulthood( 2 ), and considered to be evidence in support of the fetal origins of disease hypothesis (the Barker hypothesis), which suggests that conditions during fetal life and early childhood may increase the risk of chronic diseases in adults( 2 , 3 ).
There is also evidence that infants with low birth weight, whose postnatal catch-up growth is rapid, are more likely to become overweight or obese as children( 1 , 4 ). Another highly debated association( 5 ) is that between asthma and obesity, as is the relationship between low birth weight and impaired pulmonary function( 6 ). Nevertheless, the few studies that have investigated the relationship between the speed of weight gain in early life and the occurrence of asthma, allergies and impaired pulmonary function have yielded inconclusive results( 7 ). Birth weight above 4500 g has been shown to be both a risk and a protective factor for the development of asthma in childhood( 8 ). There is evidence that in adults, poorer weight gain in the early years of life may be related to a slight decrease in pulmonary function, and lung volume and diffusing capacity increase by 2–4 % when birth weight increases by 30 %( 9 ). Nevertheless, at 5–14 weeks after birth, impairment in pulmonary function was found to be worse in infants whose postnatal weight gain was greater (highest tertile)( 10 ).
The objective of the present study was to estimate the association between weight gain in the first two years of life and the occurrence of wheezing, asthma symptoms, serum IgE levels and pulmonary function in children aged 4–11 years. To our knowledge, no published study has yet been able to demonstrate an association between weight gain during infancy and the occurrence of asthma symptoms and atopy at school age.
Methods
Study area and population
The current cohort study (SCAALA) was conducted in Salvador, a city located in the north-east of Brazil. The participants included in the study were derived from three sequential cohorts recruited during the periods 1997, 2000 and 2003 to evaluate the impact of the introduction of a basic sanitation programme on the occurrence of diarrhoea in children between 0 and 3 years of age recruited from twenty-four small geographical areas (called sentinel areas) selected to represent the population without sanitation in the poorest neighbourhoods of Salvador. Data on study outcomes were collected in 2005 when the children were aged 4–11 years. Data collection was done by a project team from the Instituto de Saude Coletiva during all phases of the study. A detailed description of the study design and methods is provided elsewhere( 11 , 12 ). In the present analysis, we used a sub-sample of the cohort that included only children born between 1994 and 2001 who were aged less than 24 months at the start of the initial cohort study.
Data collection
All children aged between birth and less than 24 months at baseline were weighed up to three times at intervals of 6 months where possible. At least one measurement in addition to the birth measurement was done before 24 months( 12 ). Each measurement was taken in duplicate independently by trained nutritionists and the final weight was the mean of the two measurements( 13 ). Where there was more than one measurement for a child, the one nearest to 24 months of age was used in the current analysis. Children were weighed using portable electronic micro scales (Filizola®, model E-150/3P, São Paulo, Brazil) with a 150 kg capacity and accurate to within 100 g. Data for a child's date of birth and birth weight were extracted from the birth certificate. To calculate the Z-score for the weight gain between birth and up to 24 months of age, the WHO's reference curve for children up to 5 years of age was used, taking into consideration age and gender, using the following formula:
 |
in which X
2 is the measured weight of the child; X
1 is the child's birth weight; Y
2 is the reference weight; Y
1 is the reference birth weight;
is the variation between the child's birth weight and the reference birth weight for gender and age; and
is the variation between the child's weight and the reference weight for gender and age. Weight gain was considered fast when the Z-score was >0·67. This cut-off point was based on a system proposed by Ong et al.(
1
) and has been used by other investigators(
14
,
15
). In the present analysis, weight gain was considered normal when Z-scores were between −0·67 and 0·67 and slow when Z-scores were <−0·67.
Height and weight were measured for each child in 2005 using standard procedures( 13 ). BMI was calculated and analysed in 2009 using the 2006 and 2007 WHO reference standards.
Socio-economic and environmental data and information on asthma symptoms were obtained in 2005 using a standardized questionnaire adapted from the Portuguese version of the ISAAC (International Study of Asthma and Allergies in Childhood) Phase II questionnaire( 16 ).
Data on the occurrence of diarrhoea were collected during twice-weekly visits with the use of questionnaires that were completed during interviews with the children's mothers or caregivers. The data obtained referred to the 3–4 d preceding the interview. A day of diarrhoea was defined as the occurrence of three more watery or soft stools within a 24 h period, and a diarrhoea episode was identified by a minimum 3 d diarrhoea-free gap (following our definition of day of diarrhoea) to mark the beginning of a new episode. The study end point was the duration of episodes, defined as a continuous variable.
Skin tests were performed on the right forearm of each child using extracts (ALK-Abello, São Paulo, Brazil) of the following allergens: cat epithelium, dog epithelium, Dermatophagoides pteronyssinus (house dust mite), Blomia tropicalis (tropical dust mite), Blattella germanica (German cockroach), Periplaneta americana (American cockroach) and a fungi mix. Saline solution and histamine were used as negative and positive controls, respectively( 16 ). Wheal sizes were read after 15 min and the test was considered positive if the mean of the two perpendicular diameters was at least 3 mm larger than that of the negative controls. Skin prick test reactivity was considered positive when there was at least one positive response to any of the allergens tested.
Blood samples were collected for measurements of allergen-specific IgE for P. americana, D. pteronyssinus, B. tropicalis and B. germanica using commercial ImmunoCAP kits (Pharmacia Diagnostic, Uppsala, Sweden). For the purposes of the present analysis, the presence of allergen-specific IgE in each child was defined as 0 = non detectable (<0·35 kU/l) and 1 = detectable (≥0·35 kU/l).
Spirometry was performed in accordance with the recommendations of the American Thoracic Society( 17 ), using a Koko® spirometer. The volumes measured were forced vital capacity (FVC) and forced expiratory volume in 1s (FEV1). A bronchodilation test was performed by inhaling salbutamol 200 μg with spirometry being repeated after 15 min. A positive response to the bronchodilator was an increase of ≥12 % and ≥200 ml in FEV1 value compared with before inhalation of the short-acting β2 agonist( 18 ). The program used by the spirometer automatically calculated the forced expiratory ratio (FEV1:FVC) and provided predicted values for each participant in accordance with the Brazilian standard curve, taking into account the age, sex, weight and height of the child( 19 ). Pulmonary function was not evaluated in children below 6 years of age. Per cent predicted values ranged from 74 to 110 % with a mean of 98 %. Since only two children had predicted FEV1:FVC value below normal (<80 %), 98 % was used as the cut-off to define the outcome variable for pulmonary function.
Current asthma was defined as the reported occurrence of wheezing in the last 12 months and a positive response to at least one of the following: asthma at some time in the child's life, asthma in the previous 12 months, waking up at night because of wheezing, wheezing during/after exercise and four or more episodes of wheezing.
Statistical analyses
Univariate and multivariate analyses were performed using Poisson regression to assess the relationship between exposure and outcomes. Since the study outcomes (allergen skin test reactivity, serum IgE, FEV1:FVC, wheezing in the previous 12 months and asthma symptoms) were not rare events, overestimation of the odds ratio may be observed as compared with the prevalence ratio (PR). Therefore, rather than using logistic regression, multivariate Poisson regression models were defined with robust variance( 20 ) that adjusted for all variables that were statistically significant at P < 0·05. The association between weight gain and outcomes controlled for the a priori confounders of sex, child's age, maternal educational level and parental asthma. Other variables evaluated in the models were: mould in the house in the first year of life, household pets, number of persons per room, paving in the street, birth weight, duration of breast-feeding, number of older siblings and BMI. Backwards stepwise selection was then done and variables with P < 0·05 were excluded. Variables were kept in each model if they were observed to change the effect estimates for speed of growth and the main risk factor of interest in each model by more than 10 %, regardless of significance( 21 ).
Likelihood ratio tests were used to evaluate interactions and were considered to be present with P < 0·10( 21 ). According to our conceptual model, birth weight, duration of breast-feeding and age were considered to be potential effect modifiers. Differences between mean Z-scores for weight gain for study outcomes were assessed using Student's t test. Data were entered into Epi-Info version 6·4 and analysed using the statistical software package STATA version 9·0.
Ethical approval for the study was obtained from the Instituto de Saude Coletiva, Universidade Federal de Bahia, and written informed consent was obtained from the legal guardian of each child.
Results
Of 759 children aged 4–11 years assessed in 2005( 16 ), 669 who had complete data including data to allow measurement of growth during the first two years were included in the present analysis. The mean of age of the children when the measurement used in the present analysis was taken to calculate weight gain was 13·1 months (range 2·1–23·8 months). There were no differences with respect to the mean age for this measurement between children with normal, slow or fast weight gain (P = 0·603). The mean Z-score for growth rate was significantly lower in the children with a negative skin reaction. No differences were found for any of the other outcomes (Fig. 1).
Fig. 1.
Box-and-whisker plots showing weight gain Z-scores during the first two years of life according to symptoms of asthma, markers of atopy and pulmonary function in the study population: children (n 669) aged 4–11 years, Salvador, Bahia, Brazil, 1997–2005. Thick black line within the box indicates the median; the bottom and top of the box represent the 25th and 75th percentile, respectively (interquartile range); the lower and upper whiskers represent the minimum and maximum values; and circles represent outliers (FEV1, forced expiratory volume in 1 s; FVC, forced vital capacity). *Weight gain Z-score was significantly different between groups (Student's t test): P = 0.019
Weight gain in the first two years was considered fast in 29·6 % and slow in 13·9 % of the children. A total of 25·6 % of the children had wheezing in the previous 12 months, 20·0 % had asthma symptoms, 31·7 % had a positive allergen skin test and 50·6 % had a positive test for allergen-specific IgE. We provide the characteristics of the children by weight gain (Table 1) and outcome variables (Tables 2 and 3).
Table 1.
Characteristics of the study population according to weight gain group: children (n 669) aged 4–11 years, Salvador, Bahia, Brazil, 1997–2005
| Weight gain (n 669) | ||||||||
|---|---|---|---|---|---|---|---|---|
| Slow | Normal | Fast | ||||||
| (n 93; 13·9 %) | (n 378; 56·5 %) | (n 198; 29·6 %) | ||||||
| Variable | Category | n | % | n | % | n | % | P value* |
| Sex | Male | 56 | 15·5 | 196 | 54·3 | 109 | 30·2 | 0·327 |
| Female | 37 | 12·0 | 182 | 59·1 | 89 | 28·9 | ||
| Age (years) | ≥6 | 62 | 14·4 | 243 | 56·3 | 127 | 29·4 | 0·901 |
| <6 | 31 | 13·1 | 135 | 57·0 | 71 | 30·0 | ||
| Birth weight (g) | <3500 | 64 | 13·3 | 270 | 56·0 | 148 | 30·7 | 0·530 |
| ≥3500 | 29 | 15·5 | 108 | 57·8 | 50 | 26·7 | ||
| Duration of breast-feeding | Never | 21 | 11·7 | 104 | 57·8 | 55 | 30·6 | 0·662 |
| <2 months | 38 | 16·5 | 124 | 53·9 | 68 | 29·6 | ||
| ≥2 months | 34 | 13·1 | 150 | 57·9 | 75 | 29·0 | ||
| No. of older siblings | None | 26 | 9·9 | 143 | 54·6 | 93 | 35·5 | 0·006 |
| ≥1 | 67 | 16·5 | 235 | 57·7 | 105 | 25·8 | ||
| Parental asthma | No | 81 | 14·1 | 321 | 55·8 | 173 | 30·1 | 0·682 |
| Yes | 12 | 12·8 | 57 | 60·6 | 25 | 26·6 | ||
| No. of children aged <5 years in the household | ≤1 | 48 | 11·8 | 218 | 53·7 | 140 | 34·5 | 0·002 |
| >1 | 45 | 17·1 | 160 | 60·8 | 58 | 22·1 | ||
| No. of persons per room | <2 | 59 | 12·1 | 273 | 55·9 | 156 | 32·0 | 0·020 |
| ≥2 | 34 | 18·8 | 105 | 58·0 | 42 | 23·2 | ||
| Maternal schooling | High school/university | 15 | 11·5 | 67 | 51·1 | 49 | 37·4 | 0·040 |
| Secondary education | 48 | 12·8 | 215 | 57·2 | 113 | 30·1 | ||
| Illiterate or primary | 30 | 18·5 | 96 | 59·3 | 36 | 22·2 | ||
| Smoking during pregnancy | No | 80 | 13·5 | 332 | 55·9 | 182 | 30·6 | 0·222 |
| Yes | 13 | 17·3 | 46 | 61·3 | 16 | 21·3 | ||
| Mould in the home in first year of life | No | 33 | 11·5 | 164 | 56·9 | 91 | 31·6 | 0·238 |
| Yes | 60 | 15·7 | 214 | 56·2 | 107 | 28·1 | ||
| Household pets | Never had | 38 | 11·9 | 182 | 57·2 | 98 | 30·8 | 0·364 |
| Has/had | 55 | 15·7 | 196 | 55·8 | 100 | 28·5 | ||
| Paved street | Yes | 46 | 15·4 | 168 | 56·2 | 85 | 28·4 | 0·573 |
| No | 47 | 12·7 | 210 | 56·8 | 113 | 30·5 | ||
| BMI (Z-score)† | <−2 | 28 | 30·4 | 54 | 58·7 | 10 | 10·9 | <0·001 |
| ≥−2 and <+1 | 59 | 12·0 | 295 | 60·1 | 137 | 27·9 | ||
| ≥+1 | 6 | 7·0 | 29 | 33·7 | 51 | 59·3 | ||
Data are presented as number of cases (n) and prevalence (%).
*P value from χ 2 test; significant P values indicated in bold font.
†BMI Z-score: <–2 = underweight; ≥−2 and <+1 = normal; ≥+1 = overweight/obesity.
Table 2.
Characteristics of the study population according to atopy: children (n 669) aged 4–11 years, Salvador, Bahia, Brazil, 1997–2005
| Skin reactivity (n 644) | IgE > 0·35 kU/l (n 635) | ||||||
|---|---|---|---|---|---|---|---|
| Yes (n 204; 31·7 %) | Positive (n 321; 50·6 %) | ||||||
| Variable | Category | n | % | P value* | n | % | P value* |
| Sex | Male | 125 | 35·5 | 0·022 | 191 | 55·4 | 0·008 |
| Female | 79 | 27·1 | 130 | 44·8 | |||
| Age (years) | ≥6 | 133 | 32·0 | 0·785 | 209 | 50·9 | 0·838 |
| <6 | 71 | 31·0 | 112 | 50·0 | |||
| Birth weight (g) | <3500 | 139 | 30·0 | 0·149 | 230 | 50·2 | 0·787 |
| ≥3500 | 65 | 35·9 | 91 | 51·4 | |||
| Duration of breast-feeding | Never | 54 | 31·2 | 0·521 | 87 | 51·5 | 0·926 |
| <2 months | 65 | 29·3 | 109 | 49·6 | |||
| ≥2 months | 85 | 34·1 | 125 | 50·8 | |||
| No. of older siblings | None | 86 | 34·5 | 0·215 | 122 | 50·2 | 0·891 |
| ≥1 | 118 | 29·9 | 199 | 50·8 | |||
| Parental asthma | No | 177 | 31·8 | 0·829 | 277 | 50·5 | 0·903 |
| Yes | 27 | 30·7 | 44 | 51·2 | |||
| No. of children aged <5 years in the household | ≤1 | 133 | 34·1 | 0·101 | 190 | 49·6 | 0·558 |
| >1 | 71 | 28·0 | 131 | 52·0 | |||
| No. of persons per room | <2 | 164 | 35·0 | 0·003 | 238 | 51·6 | 0·378 |
| ≥2 | 40 | 22·7 | 83 | 47·7 | |||
| Maternal schooling | High school/university | 52 | 43·0 | 0·012 | 70 | 57·4 | 0·164 |
| Secondary education | 106 | 28·7 | 171 | 47·6 | |||
| Illiterate or primary | 46 | 29·9 | 80 | 52·0 | |||
| Smoking during pregnancy | No | 183 | 32·0 | 0·570 | 287 | 51·0 | 0·548 |
| Yes | 21 | 28·8 | 34 | 47·2 | |||
| Mould in the house in the first year of life | No | 78 | 28·6 | 0·146 | 125 | 46·1 | 0·054 |
| Yes | 126 | 34·0 | 196 | 53·8 | |||
| Household pets | Never had | 109 | 35·2 | 0·067 | 156 | 50·6 | 0·962 |
| Has/had | 95 | 28·4 | 165 | 50·5 | |||
| Paved street | Yes | 97 | 34·3 | 0·209 | 153 | 54·4 | 0·080 |
| No | 107 | 29·6 | 168 | 47·5 | |||
| BMI (Z-score)† | <−2 | 22 | 25·3 | 0·001 | 39 | 45·9 | 0·157 |
| ≥−2 and <+1 | 142 | 29·9 | 234 | 49·8 | |||
| ≥+1 | 40 | 48·8 | 48 | 60·0 | |||
Data are presented as number of cases (n) and prevalence (%).
*P value from χ 2 test; significant P values indicated in bold font.
†BMI Z-score: <–2 = underweight; ≥−2 and <+1 = normal; ≥+1 = overweight/obesity.
Table 3.
Characteristics of the study population according to variables related with current asthma: children (n 669) aged 4–11 years, Salvador, Bahia, Brazil, 1997–2005
| Wheezing in previous 12 months (n 669) | Asthma symptoms (n 669) | FEV1:FVC (n 508) | ||||||||
|---|---|---|---|---|---|---|---|---|---|---|
| Yes (n 171; 25·6 %) | Yes (n 134; 20·0 %) | ≤98 % (n 218; 42·9 %) | ||||||||
| Variable | Category | n | % | P value* | n | % | P value* | n | % | P value* |
| Sex | Male | 93 | 25·8 | 0·897 | 72 | 19·9 | 0·952 | 135 | 50·2 | 0·000 |
| Female | 78 | 25·3 | 62 | 20·1 | 83 | 34·7 | ||||
| Age (years) | ≥6 | 89 | 20·6 | <0·001 | 73 | 16·9 | 0·006 | 139 | 42·0 | 0·567 |
| <6 | 82 | 34·6 | 61 | 25·7 | 79 | 44·6 | ||||
| Birth weight (g) | <3500 | 113 | 23·4 | 0·044 | 87 | 18·0 | 0·040 | 141 | 39·9 | 0·041 |
| ≥3500 | 58 | 31·0 | 47 | 25·1 | 77 | 49·7 | ||||
| Duration of breast-feeding | Never | 52 | 28·9 | 0·168 | 41 | 22·8 | 0·205 | 80 | 41·0 | 0·597 |
| <2 months | 63 | 27·4 | 50 | 21·7 | 58 | 41·7 | ||||
| ≥2 months | 56 | 21·6 | 43 | 16·6 | 80 | 46·0 | ||||
| No. of older siblings | None | 58 | 22·1 | 0·103 | 45 | 17·2 | 0·139 | 92 | 46·7 | 0·170 |
| ≥1 | 113 | 27·8 | 89 | 21·9 | 126 | 40·5 | ||||
| Parental asthma | No | 137 | 23·8 | 0·011 | 104 | 18·1 | 0·002 | 176 | 40·4 | 0·004 |
| Yes | 34 | 36·2 | 30 | 31·9 | 42 | 58·3 | ||||
| No. of children aged <5 years of age in the household | ≤1 | 92 | 22·7 | 0·033 | 75 | 18·5 | 0·211 | 131 | 42·7 | 0·892 |
| >1 | 79 | 30·0 | 59 | 22·4 | 87 | 43·3 | ||||
| No. of persons per room | <2 | 123 | 25·2 | 0·729 | 96 | 19·7 | 0·704 | 165 | 44·7 | 0·181 |
| ≥2 | 48 | 26·5 | 38 | 21·0 | 53 | 38·1 | ||||
| Maternal schooling | High school/university | 34 | 26·0 | 0·883 | 25 | 19·1 | 0·767 | 45 | 47·9 | 0·509 |
| Secondary education | 98 | 26·1 | 79 | 21·0 | 120 | 41·1 | ||||
| Illiterate or primary | 39 | 24·1 | 30 | 18·5 | 53 | 43·4 | ||||
| Smoking during pregnancy | No | 149 | 25·1 | 0·427 | 117 | 19·7 | 0·545 | 194 | 42·9 | 0·993 |
| Yes | 22 | 29·3 | 17 | 22·7 | 24 | 42·9 | ||||
| Mould in the house in the first year of life | No | 54 | 18·8 | <0·001 | 40 | 13·9 | 0·001 | 86 | 40·6 | 0·366 |
| Yes | 117 | 30·7 | 94 | 24·7 | 132 | 44·6 | ||||
| Household pets | Never had | 67 | 21·1 | 0·011 | 52 | 16·4 | 0·024 | 89 | 37·9 | 0·033 |
| Has/had | 104 | 29·6 | 82 | 23·4 | 129 | 47·3 | ||||
| Paved street | Yes | 69 | 23·1 | 0·186 | 52 | 17·4 | 0·125 | 79 | 36·1 | 0·007 |
| No | 102 | 27·6 | 82 | 22·2 | 139 | 48·1 | ||||
| BMI (Z-score)† | <−2 | 17 | 18·5 | 0·176 | 14 | 15·2 | 0·152 | 16 | 25·4 | 0·000 |
| ≥−2 and <+1 | 128 | 26·1 | 97 | 19·8 | 163 | 42·9 | ||||
| ≥+1 | 26 | 30·2 | 23 | 26·7 | 39 | 60·0 | ||||
FEV1, forced expiratory volume in 1 s; FVC, forced vital capacity.
Data are presented as number of cases (n) and prevalence (%).
*P value from χ 2 test; significant P values indicated in bold font.
†BMI Z-score: <–2 = underweight; ≥−2 and <+1 = normal; ≥+1 = overweight/obesity.
Detectable allergen-specific IgE was more frequent in boys and in children who spent the first year of their life in a home in which mould was present (Table 2). A positive skin reaction was statistically more common among children with more highly educated mothers (Table 2).
The prevalence rates for wheezing and asthma symptoms were also significantly greater among children exposed to mould in the home in the first year of life (Table 3). Wheezing and asthma symptoms were significantly more common in children under 6 years of age, in those whose parents reported a history of asthma, in those who had or used to have pets and in those exposed to mould in the home in the first year of life (Table 3).
Children aged 4–11 years whose birth weight was ≥3500 g were more likely to have experienced wheezing and asthma symptoms and to have lower predicted values for FEV1:FVC. FEV1:FVC ≤98 % was significantly more common among boys, among children whose parents had a history of asthma, among those who had or used to have household pets and among those whose homes were accessed by unpaved streets. A higher proportion of children with FEV1:FVC ≤98 % (P < 0·001) and a positive skin test (P = 0·0 0 1) was observed among overweight children (BMI Z-score ≥+1; Table 3).
The prevalence of asthma symptoms was reduced by 36 % in the children with slow compared with normal weight gain in multivariate analysis (PR = 0·65; 95 % CI 0·42, 0·99; Table 4).
Table 4.
Prevalence and prevalence ratio of the study end points according to the speed of weight gain (in Z-scores) during the first two years of life: children (n 669) aged 4–11 years, Salvador, Bahia, Brazil, 1997–2005
| End point/weight gain* | n | % | PR† | 95 % CI | PR‡ | 95 % CI |
|---|---|---|---|---|---|---|
| Symptoms of asthma | ||||||
| Slow | 13 | 14·0 | 0·66 | 0·41, 1·05 | 0·65 | 0·42, 0·99 |
| Normal | 80 | 21·2 | 1·00 | – | 1·00 | – |
| Fast | 41 | 20·7 | 0·98 | 0·71, 1·34 | 1·00 | 0·71, 1·40 |
| Wheezing in the previous 12 months | ||||||
| Slow | 20 | 21·5 | 0·79 | 0·52, 1·19 | 0·80 | 0·55, 1·15 |
| Normal | 103 | 27·2 | 1·00 | – | 1·00 | – |
| Fast | 48 | 24·2 | 0·89 | 0·66, 1·20 | 0·91 | 0·67, 1·25 |
| Forced expiratory ratio (FEV1:FVC) | ||||||
| Slow | 26 | 39·4 | 0·96 | 0·75, 1·22 | 1·00 | 0·80, 1·26 |
| Normal | 122 | 41·1 | 1·00 | – | 1·00 | – |
| Fast | 70 | 48·3 | 1·17 | 0·92, 1·50 | 1·05 | 0·80, 1·38 |
| Skin reactivity to allergens | ||||||
| Slow | 24 | 26·4 | 0·86 | 0·56, 1·35 | 0·86 | 0·57, 1·30 |
| Normal | 110 | 30·5 | 1·00 | – | 1·00 | – |
| Fast | 70 | 36·5 | 1·20 | 0·91, 1·56 | 1·07 | 0·81, 1·42 |
| IgE detectable for allergens | ||||||
| Slow | 47 | 52·2 | 1·05 | 0·85, 1·30 | 1·02 | 0·81, 1·30 |
| Normal | 177 | 49·9 | 1·00 | – | 1·00 | – |
| Fast | 97 | 51·1 | 1·02 | 0·88, 1·19 | 0·98 | 0·82, 1·16 |
n, number of cases; PR, prevalence ratio; FEV1, forced expiratory volume in 1 s; FVC, forced vital capacity.
Significant associations are indicated in bold font.
*Weight gain: slow = Z-score <−0·67; normal = Z-score ≥−0·67 to ≤0·67; fast = Z-score >0·67.
†Crude prevalence ratio.
‡Prevalence ratio adjusted for sex, age, maternal schooling, parental asthma, birth weight, duration of breast-feeding, smoking during pregnancy, mould in the house in the first year of life, BMI, number of older siblings, household pets, number of persons per room, number of children aged <5 years in the household and paving in the street.
Likelihood ratio tests for interaction were not statistically significant for birth weight, duration of breast-feeding and age for any of the outcomes.
Discussion
Our main study finding was that slow weight gain in the first two years of life was negatively associated with asthma symptoms in late childhood. We have already shown in this study population that weight gain in the first years of life is associated with BMI at age 4–11 years( 22 ) and that overweight children have an increased risk of asthma symptoms( 23 ). These findings contribute to the body of evidence showing that slow weight gain in the first years of life may not only be a protective factor against becoming overweight but also be protective against asthma. There was no statistically significant association between atopy and weight gain and it is possible that the mechanism involved in asthma is independent of atopy.
Few studies have evaluated the association between somatic growth in early childhood and asthma or lung function at school age or in adulthood( 7 – 9 , 24 – 26 ). Fast growth in early childhood was associated with wheezing( 7 , 24 ) in scholars. However, in these studies, growth rate was not measured in the same way as done here. This is due to the use of different reference charts, limiting our ability to compare results. Although we observed an association between weight gain and current asthma, we did not see an association with current wheezing in the present study. We believe that our definition for current asthma may better represent true asthma cases than wheezing alone, because these criteria are more specific than wheezing in the last 12 months, the most common criterion used for ISAAC. We used also wheezing in the previous 12 months alone to permit comparability between the studies.
Studies conducted in different populations have shown an effect of weight gain during infancy on pulmonary function in early( 10 , 25 ) or late( 9 ) life. A prospective study conducted in Australia concluded that fast weight gain between the first and the twelfth months of life, particularly in children of low birth weight, was associated with decreased pulmonary function at 12 months and increased symptoms of transient asthma, suggesting an important association between somatic growth and pulmonary function in childhood( 25 ). Likewise, Lucas et al. reported that when weight gain and pulmonary function were evaluated between 5 and 14 weeks of life, higher rates of weight gain were positively associated with impaired pulmonary function( 10 ). Nevertheless, in the study conducted by Hancox et al., weight gain in the first three years of life was positively associated with better pulmonary capacity (functional residual capacity) in young adults( 9 ).
The mechanisms involved in the association between fast growth and impaired pulmonary function are not fully understood. It is known that postnatal catch-up growth, as reflected by higher growth rates, has been documented in children who suffered intra-uterine growth restriction. It is also known that the environmental factors that act pre- and postnatally, particularly towards the end of pregnancy and in the first months of life, may affect alveolar development with possible long-term structural and functional damage. In early pregnancy, environmental factors may impair correct cell division in the airways, leading to abnormalities in programming pulmonary function( 27 ). Nevertheless, in some studies, low birth weight was not a prerequisite for the occurrence of fast growth and subsequent impaired pulmonary function( 25 ). Unfortunately, the effect of low birth weight could not be analysed in the current study sample due to the small number of children with this condition. Another hypothesis is that children with normal birth weight and exposed to a hyperenergetic diet gain weight rapidly, but rapid growth is not accompanied by a parallel improvement in pulmonary function because of defective airways or air space development or the inability of airway growth to keep pace with somatic growth( 25 ). In the present study, conducted in the general population, there were only two children with abnormal lung function (FEV1:FVC <80 %), limiting our capacity to detect differences between weight gain and impairment in lung function.
There is evidence that children who experience postnatal catch-up growth are more likely to be obese at 5 years of age than children with normal growth( 1 ), and high levels of serum insulin and leptin have also been found in overweight children. Leptin is an adipose-derived hormone whose inflammatory effect may alter the balance of Th1 and Th2 cytokines in obese individuals by affecting Th1 cell differentiation and the production of pro-inflammatory cytokines such as TNF-α. Thus, high levels of serum leptin could be associated with the pathogenesis of asthma in overweight children( 5 , 28 – 30 ) by the induction of a pro-inflammatory state in which inflammation in the airways may be increased, leading to alterations in pulmonary physiology. In the population of children studied here, overweight was less frequent among those with a slow weight gain( 22 ). It is possible that that lower leptin levels may have been present in these children and, consequently, they may have had a lower risk of wheezing and asthma. This hypothesis will need to be tested in future studies that measure levels of serum leptin.
Some limitations present in previous studies were not an issue in our study. In our study, prospective data were obtained directly from the children's parents or guardians. In addition, sample size was adequate and the same methodology was used for data collection from baseline onwards, with most of the members of the technical field team remaining throughout the entire project. The availability data for of total and allergen-specific IgE and spirometry was a strength compared with previous studies conducted under similar conditions and with similar populations. We were also able to control our analyses for multiple socio-economic, environmental and other confounding factors related to the health of the child and to the exposure and outcomes. A limitation is that it is not possible to make inferences on causality because data on the study outcomes were not obtained in infancy, thereby not allowing us to distinguish between those who did and did not have study outcomes at baseline. Beyond this, another limitation is that we did not have the total of children evaluated for outcomes in 2005 with anthropometric outcomes (weight gain) collected in infancy. The baseline of the cohort about asthma was in 2005 and on this occasion 1445 children were sorted by three previous cohorts, but we have previous information about weight gain on only 669 children. In this cohort of a low-income community, it was not feasible to follow up each individual in the cohort periodically to evaluate study outcomes, although it is difficult to predict at what age such outcomes might be predicted to appear in childhood.
Conclusion
Our findings suggest that in a population of children living in poor neighbourhoods in a Latin American city, slow weight gain in infancy may be protective against asthma. Since asthma and obesity are problems that begin in pre-schoolers, interventions to maintain adequate weight but avoid excessive weight gain in early infancy could have several benefits including a reduction in asthma symptoms in late childhood.
Acknowledgements
Sources of funding: The present study was funded by The Wellcome Trust, UK under the HCPC Latin America Excellence Centre Programme (Ref. 072405/Z/03/Z). The previous studies conducted with the same cohort were supported by the Programa de Núcleo de Excelência (PRONEX-CNPq/MCT), Brazil (Contract no. 66.1086/1998-4) and by the Bahia State Government Department of Urban Development, Brazil. S.d.M.S. was supported by the Foundation for the Support of Research in the State of Bahia (FAPESB), Brazil (1941/2006). Conflicts of interest: The authors have no conflict of interest to declare. Ethics: Ethical approval for this study was provided by the Internal Review Board of the Institute of Collective Health, Federal University of Bahia, by the National Commission on Ethics in Research (CONEP), Brazil, and by the London School of Hygiene and Tropical Medicine. Authors’ contributions: S.M.A.M. was responsible for writing this manuscript; M.L.B., L.C.R. and A.A.C. obtained the funding and coordinated the study; M.S.P. and M.L.B. designed the methodology for data collection; M.S.P. coordinated and S.M.A.M. participated in collecting the anthropometric data; S.d.M.S. supervised and participated in collecting the spirometry test data; N.M.A.-N. supervised the detection of IgE antibodies; S.R.J., S.M.A.M., R.L.F. and S.R.D.M.S. conducted the statistical analyses; A.M.O.A., S.M.A.M., A.A.C. and S.D.I. contributed by critically reviewing the manuscript. All authors contributed to reviewing the manuscript and are in agreement with respect to its submission. Acknowledgements: The authors wish to express their gratitude to the children and parents who participated in this study. They also thank Dr Philip J. Cooper for review of the manuscript.
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