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On-line version ISSN 1678-4464
Cad. Saúde Pública vol.24 suppl.2 Rio de Janeiro 2008
Sintomas de depressão pós-parto e interrupção precoce do aleitamento materno exclusivo nos dois primeiros meses de vida
Maria Helena HasselmannI; Guilherme L. WerneckII; Claudia Valéria Cardim da SilvaI
IInstituto de Nutrição, Universidade do Estado do Rio de Janeiro, Rio de Janeiro, Brasil
IIInstituto de Medicina Social, Universidade do Estado do Rio de Janeiro, Rio de Janeiro, Brasil
This study evaluates the association between postpartum depression and interruption of exclusive breastfeeding in the first two months of life. Cohort study of 429 infants < 20 days of age to four primary health care units in Rio de Janeiro, Brazil. Interruption of exclusive breastfeeding (outcome) was defined as the introduction of water, other types of liquids, milk, or formulas or any food. Postpartum depression was assessed using the Edinburgh Post-Natal Depression Scale. Associations between variables were expressed as prevalence ratios (baseline) and risk ratios (follow-up), with their respective 95% confidence intervals, estimated by Poisson regression with robust variance. Children of mothers with postpartum depressive symptoms were at higher risk of early interruption of exclusive breastfeeding in the first and second months of follow-up (RR = 1.46; 95%CI: 0.98-2.17 and RR = 1.21; 95%CI: 1.02-1.45, respectively). Considering mothers that were exclusively breastfeeding at the first month, postpartum depression was not associated with interruption of exclusive breastfeeding in the second month (RR = 1.44; 95%CI: 0.68-3.06). The results indicate the importance of maternal mental health for the success of exclusive breastfeeding.
Nutritional Epidemiology; Breast Feeding; Postpartum Depression
Avaliou-se a associação entre depressão pós-parto e interrupção precoce do aleitamento materno exclusivo nos dois primeiros meses de vida. Estudo de coorte com 429 crianças < 20 dias de idade em quatro unidades de saúde no Rio de Janeiro, Brasil. Considerou-se como interrupção precoce do aleitamento materno exclusivo a introdução de chá, água, suco, leite artificial ou qualquer outro alimento. Na avaliação da depressão pós-parto utilizou-se a Edinburgh Post-natal Depression Scale. Associações foram expressas como razões de prevalências (linha de base) e riscos relativos (primeiro e segundo meses de vida) e respectivos intervalos de 95% de confiança estimados via regressão de Poisson com variância robusta. Filhos de mulheres com sintomas de depressão pós-parto apresentam maior risco de interrupção precoce do aleitamento materno exclusivo nos dois meses de seguimento (RR = 1,46; IC95%: 0,98-2,17 e RR = 1,21; IC95%: 1,02-1,45, respectivamente). Entre mães que amamentam exclusivamente até o primeiro mês de vida, depressão pós-parto não se associou à interrupção precoce do aleitamento materno exclusivo (RR = 1,44; IC95%: 0,68-3,06). Esses achados apontam para a importância da saúde mental materna no sucesso do aleitamento materno exclusivo.
Epidemiologia Nutricional; Aleitamento Materno; Depressão Pós-Parto
According to the World Health Organization, malnutrition is associated with 60% of the 10.9 million annual deaths in children under 5 years. In the first year of life, two-thirds of these deaths are associated with inadequate feeding practices, mainly those resulting from early weaning 1. Breastfeeding helps reduce the incidence of asthma and allergies and promotes growth and emotional and cognitive development 2. Additionally, recent studies suggest that upon reaching adulthood, breastfed children tend to present lower blood pressure and cholesterol and lower prevalence rates for overweight/obesity and type-2 diabetes 3,4,5,6.
In Brazil, despite improvement, studies have shown that only 35% of infants enjoy exclusive breastfeeding during the first four months of life (therefore less time than the recommended target of six months of exclusive breastfeeding) 1,7,8. The literature on determinants of feeding practices in the first year of life (including breastfeeding and its duration) has emphasized the psychosocial factors involved in this process, particularly a possible association between postpartum depression and interruption of breastfeeding 9,10.
Several recent articles show an association between maternal depression and breastfeeding duration 11,12,13, but the findings are conflicting. For example, according to Henderson et al. 14, postpartum depression has a negative impact on duration of breastfeeding. According to Gröer 15, mothers that breastfeed experience less depression and rage and more positive life events than formula-feeders. Other studies show that depressive symptoms are not predictors of intention to breastfeed 16,17. Misri et al. 18 conclude that the onset of postpartum depression precedes interruption of breastfeeding, but the severity of depression does not appear to influence duration of breastfeeding.
In Brazil, studies have shown postpartum depression prevalence rates ranging from 12% to 37%, depending on the measurement instrument and cutoff point used in the postpartum evaluation 19,20,21,22,23. There are few studies on the theme in Brazil, with conflicting results. According to Falceto et al. 24, mothers presenting psychiatric problems in the first month postpartum have twice the odds of interrupting breastfeeding early. More recently, Vitolo et al. 23 corroborated the relationship between maternal depression and interruption of exclusive breastfeeding. Meanwhile, a study in the city of São Paulo showed that breastfeeding patterns were not associated with postpartum depression 20.
To help elucidate this relationship, the current study investigated the role of postpartum depression in the risk of early interruption of exclusive breastfeeding during the first months of life.
Material and methods
The information analyzed in this study is from a broader investigation whose main focus is the role of family violence, maternal care for children, and social support in the determination of infant growth. This is a prospective study monitoring the growth of 550 newborns selected during the first year of life at primary health clinics under the Rio de Janeiro Municipal Health Secretariat.
Study design and population
This was a prospective cohort of 429 children < 20 days of age brought to four primary health clinics for the heel stick test or BCG vaccination from June 2005 to December 2006 and that participated in the two complementary data collection stages, the first during the baseline visit and the second 20 to 40 days later (first month of life). The children were evaluated again during a third phase, 20 to 40 days after the second visit (second month of life).
The primary care clinics participating in the study were selected intentionally, as a function of the number of consultations in the Mother-Infant Health Promotion Program of the Rio de Janeiro Municipal Health Secretariat and the availability of a physical area for conducting the interviews.
Selection of participants occurred when the child was received at the clinic. The selected children represent a subset of the total number of children received, as a function of the availability of interviewers and work shifts, covering Monday through Friday mornings.
The study has a power of 80% for detecting as significant differences (alpha error of 5%) a prevalence ratio or risk ratio of 2.0, considering a prevalence of 15% for early interruption of breastfeeding among the unexposed.
Measurement and data collection
The information was obtained using a face-to-face interview with the child's mother. The study's principal investigator (M. H. H.) coordinated the field team's training. Throughout the data collection phase there was continuous supervision of interviewers, in addition to systematic retraining. In the three study phases, the evaluation included questions on the current breastfeeding situation ("From yesterday morning until this morning, did you breastfeed your baby?"), in addition to questions on the use of other types of milk, water, teas, juice, and other foods. The study outcome was early interruption of exclusive breastfeeding defined as the non-utilization of exclusive breastfeeding, i.e., when the child received any type of liquid or solid food, regardless of whether he or she was still receiving the mother's breast milk 25.
The study's main exposure variable, the suspicion of postpartum depression, was measured using the Portuguese-language version of the Edinburgh Post-Natal Depression Scale, applied face to face with cards, using > 12 as the cutoff point 26.
The other study variables were structured according to a hierarchical approach, using as the reference a theoretical-operational model on the determinants of early interruption of exclusive breastfeeding (Figure 1).
This model includes the following co-variables: demographic (child's gender and age in days); socioeconomic (maternal schooling, < 4 years and > 4 years); and an indicator of housing conditions, derived from a score based on the following household variables: crowding; construction material, flooring, electricity, type of internal plumbing, source of water, and garbage collection, classified as unsatisfactory (score < 8) or satisfactory (score > 8) 27; maternal variables (age < 18 and > 18 years), health care during pregnancy (number of prenatal visits), childbirth conditions (mode of delivery: natural versus cesarean or forceps), and child's condition at birth (birth weight: < 2,500g or > 2,500g; and prematurity: yes or no). The interview also recorded the mother's work, marital status, social network, and social support. Maternal work was evaluated with the question "Are you [the child's mother] currently working outside the home?" (yes or no). Marital status was recorded with a question having 6 different alternatives and categorized as living versus not living with husband/partner. Social network was recorded with the question "How may relatives do you feel comfortable with and can talk about almost everything?", arranged in order in the analysis: 0, 1, 2, and 3 or more relatives. Social support was measured by a social support scale prepared for the Medical Outcomes Study 28 and adapted to Portuguese 29,30. To calculate the social support scale's standardized scores, points were ascribed to each possible answer, varying from one (never) to five (always) for the 19 questions comprising the questionnaire. The scores were calculated as the sum of the total points for the answers in each of the five dimensions covered by the scale and divided by the maximum number of possible points that could be obtained in the same dimension, in order to standardize the results for all the dimensions, since these consisted of different numbers of questions. The result for the ratio (total points obtained/maximum possible points for the dimension) was multiplied by 100. The variable included in the analyses was obtained by the sum of the standardized scores for the five dimensions, divided by five, having been dichotomized as < 75 (unsatisfactory) and > 75 standardized points (satisfactory).
The study was approved by the Institutional Review Board of the Institute of Social Medicine, Rio de Janeiro State University (UERJ).
Data processing and analysis
Data were stored in Epi Info 6.4 (Centers for Disease Control and Prevention, Atlanta, USA), and 20% of the keying-in was reviewed.
The analytical strategy began with calculation of baseline prevalence and cumulative incidences (at one and two months of age) for early interruption of exclusive breastfeeding, according to exposure variable categories. Risk of early interruption of exclusive breastfeeding was also calculated according to exposure variable categories, conditioned according to whether the infant was in exclusive breastfeeding in the first month of life. Thus, the study evaluates the early interruption of exclusive breastfeeding from four perspectives: (1) baseline prevalence; (2) cumulative incidence until the first month of life; (3) cumulative incidence until the second month of life; and (4) cumulative incidence at two months among infants still on exclusive breastfeeding at one month.
Simple associations between outcomes and each exposure variable were expressed as prevalence ratios (baseline) and relative risks (at one and two months of age) and their respective 95% confidence intervals (95%CI). Multivariate analyses were based on a Poisson regression model with robust variance in order to express independent associations as prevalence ratios (baseline) and relative risks (at one and two months of age) and their respective 95%CI 31.
The modeling process followed the logic of the determination model's hierarchical structure, and each variable's effect on the outcome was controlled for the variables at the same (or higher) levels. At each hierarchical level, variables were incorporated in a multivariate model, and the only variables submitted as potential confounders to the multivariate models at the subsequent levels were those whose association with the outcome remained within a significance level of up to 20% (p < 0.20), after backwards stepwise procedures, always controlling for variables from the higher levels. Associations between the outcome and the study variables were defined as statistically significant at p < 0.05. Data analysis used Stata/SE 9.1 (Stata Corp., College Station, USA).
Mean age of the 429 children participating in the first interview (baseline) was 9.1 days (SD = 3.9). Mean age was 34.2 days (SD = 4.7) at the second interview (first month) and 62.8 days (SD = 2.8) at the second month.
Baseline prevalence of early interruption of exclusive breastfeeding was 20.8%. Among the 295 children in exclusive breastfeeding at baseline and that returned for the second interview after 20 to 40 days, risk of early interruption of exclusive breastfeeding was 33.2%. Accumulated incidence of early interruption of exclusive breastfeeding was 57.9% at the second month of life. Meanwhile, among the 138 children that remained on exclusive breastfeeding until the first month of life and that returned for the following visit, risk of early interruption of exclusive breastfeeding was 26.1%.
Table 1 shows the variables associated with baseline prevalence of early interruption of exclusive breastfeeding, which was more prevalent among older infants and some 60% higher among those with unsatisfactory living conditions. Early weaning was more common among premature infants. Social network, measured by the number of relatives with whom the mother felt comfortable talking about almost any subject, was inversely related to weaning prevalence, while postpartum depression was associated with an increase of some 80%.
Table 2 shows the variables associated with early interruption of exclusive breastfeeding in the first month of life. Marital status (living without husband/partner) and postpartum depression were associated with an increase of some 40% in the risk of early interruption of exclusive breastfeeding during this period, but the 95%CI for the relative risks also indicate that these results were consistent with a lack of association.
Table 3 shows that age and postpartum depression were the only variables associated with cumulative incidence of early interruption of exclusive breastfeeding up to two months.
Table 4 shows that among the infants that remained on exclusive breastfeeding up to the first month of life, age and prematurity were the only factors significantly associated with early interruption of exclusive breastfeeding.
The results of this study show that children of mothers with symptoms of postpartum depression present an increased risk of early weaning, both in the first days of life and in the following two months, even after controlling for potential confounders. However, considering mothers that continue exclusive breastfeeding up to one month, presenting symptoms of postpartum depression at the beginning of follow-up does not constitute a risk for the early introduction of other foods in the second month. These findings are consistent with other studies 12,23,32,33. According to Henderson et al. 14, women with postpartum depression at any time in the 12 months of follow-up showed greater probability of suspending breastfeeding than women without depression. Additionally, according to Hatton et al. 10, mothers with depressive symptoms at six weeks after childbirth are less likely to breastfeed. Specifically, postpartum depression appears to be associated with mothers' increased difficulty in initiating breastfeeding 10.
Interestingly, socioeconomic factors like schooling and housing conditions do not prove relevant in determining early interruption of exclusive breastfeeding in the two months of follow-up, a tendency that appears to be corroborated by other studies 34,35,36. For example, Scott et al. 35, investigating changes in the determinants of initiation of breastfeeding, conclude that psychosocial factors like maternal perception of the father's attitudes (and her own) in relation to breastfeeding were stronger predictors of breastfeeding than socio-demographic and biomedical variables. More recently, Carvalhaes et al. 36, studying factors associated with exclusive breastfeeding in Botucatu, São Paulo State, showed that socioeconomic and demographic variables were not associated with early interruption of exclusive breastfeeding in infants < 4 months, but only use of a pacifier and report of difficulties in breastfeeding. The role of proximal factors appears to be more evident in the determination of exclusive breastfeeding than that of more distal variables. Unfortunately, in the current study, this more proximal dimension of the theoretical model was not investigated. However, it is possible that postpartum depression not only reflects maternal psychological and emotional profiles, but also maps aspects related to "difficulties in breastfeeding" and perhaps even "use of a pacifier". It is not difficult to imagine that mothers who present depressive symptoms in the post-natal also experience greater difficulties in breastfeeding and thus tend to offer a pacifier to their infants. According to Dennis 37, due to their emotional state, depressed mothers may be more susceptible to "giving a bottle" to their infants 38.
Another possible explanation refers to the relationship between postpartum depression and variables pertaining to mothering and mother-infant interaction. Dennis & MacQueen 13, reflecting on one of the possible pathways producing this relationship, highlight the importance of postpartum depression's effects on the mother's emotional state, interfering in her availability for mothering or relating to and interacting with her child. Immediate postpartum depressive symptoms can lead to early interruption of breastfeeding due to feelings of low self-esteem and self-confidence, which can generate an exaggerated perception of the mother's difficulties in breastfeeding. This suggests that mothers who suffer postpartum depression can lose their confidence in their maternal role and not perceive the benefits of breastfeeding 38. According to Pippins et al. 11, further research is needed to understand the most relevant and persistent symptoms before or during pregnancy that are associated with the decision to breastfeed.
Another area explored in the literature to explain this relationship refers to the depressed mother's negative perception of the child's behavior. According to Dennis & MacQueen 13, postpartum depression involves decreased satisfaction in these women in breastfeeding their children. These mothers apparently perceive their infants as insecure after nursing, which leads them to view their own breast milk as insufficient and thus consider the need for supplementation.
The protective effect of social networks deserves attention. Mothers who report having relatives in whom they trust and with whom they can talk about nearly everything show lower prevalence rates for early interruption of exclusive breastfeeding at the beginning of follow-up. Meanwhile, in the infant's second month of life (Table 4), marital status appears relevant in the determination of weaning, i.e., living with a husband/partners protects from early weaning. According to Barreira & Machado 39, family members can potentially exert the greatest impact on initiating and continuing to breastfeed. Recent studies have highlighted the role of paternal participation in the success of breastfeeding 24,40,41. For example, Falceto et al. 24 observe that a mother who feels her partner actively supporting breastfeeding (talking about its importance or facilitating her role) tends to breastfeed longer. Vari et al. 41 suggest that social support that incorporates pre and post-natal contacts and that are mediated by health professionals can influence the duration of exclusive breastfeeding and the woman's satisfaction with this practice.
Four comments of a methodological nature deserve highlighting. The first relates to the population group being studied. The women interviewed in this study attend public health clinics in the city of Rio de Janeiro, and a large share of them had been exposed to health promotion activities and encouragement for breastfeeding. Thus, this group of women could be expected to be more prone to exclusive breastfeeding and perhaps less exposed to the risk of postpartum depression, due to the support offered by the health professionals involved in these programs. In this sense, any attempt to extrapolate these findings to women not supported with similar conditions should be done with caution, since the putative relationship between postpartum depression and early interruption of exclusive breastfeeding may not be as evident in situations in which both postpartum depression and weaning are more frequent.
The second aspect to be considered is how breastfeeding was measured (24-hour recall), which may have led to an outcome misclassification bias. This measurement only reveals what the infant ingested in the previous 24 hours and may include both children that were really in exclusive breastfeeding as well as others who ingested breast milk only during that 24-hour recall period, but who at some moment tried or who systematically ingest other types of food beside the mother's breast milk. One cannot assess with certainty the direction and potential magnitude of this bias, but there is no strong indication that such misclassification is differential in relation to exposure, which suggests the possibility that the data presented here actually underestimated the association. In addition, this form of outcome measurement does not allow evaluating the effect of postpartum depression on the duration of breastfeeding.
A third possible limitation refers to the moment at which the study's central exposure (postpartum depression) was measured, namely in the immediate postpartum. Boyd et al. 42 suggest that this scale would be more appropriate for use as close as possible to the second week postpartum, and that its application closer to delivery might not be capable of detecting the phenomenon in all its intensity. Still, there is evidence that earlier measurement is predictive of depression in subsequent months 43,44. In the current study, the interview on postpartum depression was held on average 9 days after delivery. As for the cutoff point used here, a validation study in Brazil showed a sensitivity of 72% and specificity of 88% 26.
Losses to follow-up, which totaled 13.2% at one month and 28.86% at two months of life, are another possible limitation to this study's validity. It is conceivable that mothers with depressive symptoms experience greater difficulty in attending follow-up interviews, which could represent a kind of selective follow-up loss if they were also more prone to early interruption of breastfeeding, as appears to be supported by the literature on the theme. If this conjecture is true, the associations presented here between postpartum depression and early interruption of exclusive breastfeeding may have been underestimated. However, no significant difference was observed between the proportion of women with depressive symptoms among losses (18.5%) and those who remained in follow-up (17.5%) (p = 0.836). Significant differences were only observed for age (p = 0.015), mode of delivery (p = 0.083), and marital status (p = 0.079), whereby the infants who remained in the follow-up were younger, more frequently born of cesarean or forceps delivery, and children of mothers who lived with a husband/partner. The impact of these heterogeneities on the study's results is difficult to assess, and one should be cautious in interpreting the findings, especially given the number of losses observed during the second period of follow-up (i.e., there is no way of ensuring that the mechanisms generating the losses are ignorable).
Finally, we emphasize the contribution of these results to the development of health promotion activities in relation to postpartum depression and encouragement for exclusive breastfeeding. The findings point to the importance of a special view towards maternal mental health in the postpartum, like other health conditions and quality of life for these women.
All the authors participated in the different stages of the research and the design and drafting of the article. M. H. Hasselmann coordinated the study, conducted the data analysis, and wrote the first draft of the article. G. L. Werneck contributed to the drafting of the article and data analysis and interpretation. C. V. C. Silva assisted in interpreting the results and drafting the article. The final version was reviewed and approved by all the authors.
This study was partially funded by the Brazilian National Research Council (CNPq; grant 50.6194/2004-3) and the Rio de Janeiro State Research Foundation (FAPERJ grant E-26/170.848/2005). The authors wish to thank the Children's Health Program of the Rio de Janeiro Municipal Health Secretariat and the administrators and professionals from the participating clinics. The project was conducted in partnership with the Institute of Nutrition, Rio de Janeiro State University (UERJ), Institute of Social Medicine/UERJ, and Children's Health Program of the Rio de Janeiro Municipal Health Secretariat.
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M. H. Hasselmann
Departamento de Nutrição Social, Instituto de Nutrição
Universidade do Estado do Rio de Janeiro
Rua São Francisco Xavier 524, 12º andar
Rio de Janeiro, RJ
Submitted on 21/Aug/2007
Final version resubmitted on 25/Feb/2008
Approved on 10/Mar/2008