Partner relationship satisfaction and maternal emotional distress in early pregnancy
© Røsand et al; licensee BioMed Central Ltd. 2011
Received: 2 June 2010
Accepted: 14 March 2011
Published: 14 March 2011
Recognition of maternal emotional distress during pregnancy and the identification of risk factors for this distress are of considerable clinical- and public health importance. The mental health of the mother is important both for herself, and for the physical and psychological health of her children and the welfare of the family. The first aim of the present study was to identify risk factors for maternal emotional distress during pregnancy with special focus on partner relationship satisfaction. The second aim was to assess interaction effects between relationship satisfaction and the main predictors.
Pregnant women enrolled in the Norwegian Mother and Child Cohort Study (n = 51,558) completed a questionnaire with questions about maternal emotional distress, relationship satisfaction, and other risk factors. Associations between 37 predictor variables and emotional distress were estimated by multiple linear regression analysis.
Relationship dissatisfaction was the strongest predictor of maternal emotional distress (β = 0.25). Other predictors were dissatisfaction at work (β = 0.11), somatic disease (β = 0.11), work related stress (β = 0.10) and maternal alcohol problems in the preceding year (β = 0.09). Relationship satisfaction appeared to buffer the effects of frequent moving, somatic disease, maternal smoking, family income, irregular working hours, dissatisfaction at work, work stress, and mother's sick leave (P < 0.05).
Dissatisfaction with the partner relationship is a significant predictor of maternal emotional distress in pregnancy. A good partner relationship can have a protective effect against some stressors.
Becoming a parent or expanding the family with a new child is an important life event that involves not only the pregnant woman, but also the partner and the extended family. For most women, pregnancy is a happy experience associated with positive expectations, but worries and concerns also increase. Many women feel vulnerable during pregnancy. They become more dependent upon their partner and support from family and friends, especially other women becomes more important during this time [1–3]. Previous studies on pregnant women's mental health have examined both specific aspects such as depression, and broader concepts such as emotional distress. Recent research suggests that antenatal depression is as prevalent as postpartum depression (PPD) [4–6]. A review published in 2004 based on 21 studies (19,284 respondents), found that the prevalence of depression during pregnancy was 7.4%, 12.8% and 12.0% during the first, second and third trimester respectively . The severity and nature of the depressed mood does not seem to differ significantly pre and post birth .
Recognition of maternal emotional distress during pregnancy and the identification of risk factors for such distress are of considerable clinical importance because mental health problems can affect both the foetus and the mother. Anxiety and depression during pregnancy have been associated with poor pregnancy outcomes, such as preterm delivery, low infant birth weight, and small-for-gestational-age infants [2, 7]. In addition, depressive symptoms during pregnancy are a significant predictor of postnatal depression  and breastfeeding status at six months postpartum . One longitudinal study showed that antenatal depression bore a stronger relationship with negative child outcomes measured in the early school years than did maternal depression at any time point postpartum .
Relative to the numerous studies on risk factors for PPD, few studies have reported results on the risk factors for anxiety and depression symptoms during pregnancy. Some investigations have shown that the risk for depression (or, in some studies, poor global mental health) during pregnancy is associated with poor relationship with the partner [11, 12], low or absent support from the partner [11, 13], low support from extended family/friends [11, 14], demographic factors such as low education , single status [11, 14, 15], financial hardship [11, 16], young maternal age [12, 17], many children in the household , high life stress [11, 13], obstetric factors like first pregnancy, a past history of abortion , unintended pregnancy [11, 20], poor pregnancy outcomes  and a history of depression [11, 16, 20]. A few studies have reported a significant effect of smoking [11, 21], sleep quality  and poor somatic health [14, 17] on depression symptoms in early pregnancy.
Most of these studies suffered from small sample sizes, and in some of them, the study population comprised of financially impoverished women [13, 15]. Many of the studies are relatively old. One exception is a recent Swedish study of 3011 pregnant women, which demonstrated that lack of support from the partner, more than two stressful life events in the year prior to the pregnancy and having a native language other than Swedish were the most important predictors for depression in early pregnancy .
From a prevention perspective, it is important to explore possible protective factors against emotional distress in pregnancy. In accordance with the buffer hypothesis , some factors may help to protect against severe effects of certain strains. It has been documented that social support is an important protective factor regarding the individual's ability to handle stressful events and recovery after such events [25–27]. Thus, some types of stress will probably be tolerable for women who have good social support and high partner relationship satisfaction. Such buffer effects are usually tested as interaction effects between risk and protective factors.
To our knowledge, no other large-scale study has included such a large number of risk factors for maternal emotional distress in pregnancy as does ours. Herein, we report the results of a study consisting of 51,558 pregnant women in Norway that focused on factors related to the partner, family, and organizing everyday life. The first aim of the study was to identify risk factors for maternal emotional distress in pregnancy. We explored the contribution of 37 potential risk factors including relationship satisfaction, demographic characteristics, work-related stress, somatic diseases, negative life events and daily strain factors. The effect sizes for these risk factors were estimated. Our main hypothesis was that relationship satisfaction would be of particular importance for the women in our sample. The second aim was to assess whether high relationship satisfaction protects against severe effects of certain stressful events. We hypothesised that relationship satisfaction would protect against severe effects of certain risk factors.
Descriptive statistics for MoBa sample vs population
University, lower degree
University, higher degree
The current study had access to the first wave of participants including 51,558 women who had returned the questionnaires filled in during the 17th week of gestation. As expected, due to the large number of questions included in the questionnaire, some items had not been answered. Therefore, we chose to impute values for missing scores according to specific criteria (see below). Following the imputation procedures, 49,425 women with complete datasets were included in the analyses. The study was approved by the Regional Committee for Medical Research Ethics and the Norwegian Data Inspectorate.
Main outcome variable
Maternal emotional distress was measured using a short version of the Hopkins Symptom Checklist (SCL-25) . The SCL is a self-administered instrument designed to measure symptoms of anxiety and depression . The five item version (SCL-5) correlates 0.92 with the original version . SCL-5 has shown to have good psychometric properties [34, 36]. The five anxiety and depression items is treated as a global measure of mental health, hereafter termed emotional distress. The SCL-5  consisted of the following items: "Have you been bothered by any of the following during the last two weeks: 1) Feeling fearful; 2) Nervousness or shakiness inside; 3) Feeling hopeless about the future; 4) Feeling blue; 5) Worrying too much about things?". The response categories range were 1 = not bothered, 2 = a little bothered, 3 = quite bothered, and 4 = very bothered. The Cronbach alpha reliability for the SCL-5 was demonstrated to be 0.80. The SCL-scores were highly skewed with a tail to the right (mean = 1.26, SD = 0.39, skewness = 2.45, kurtosis = 8.21), and were ln-transformed to obtain closer to normal distribution. The dependent variable was standardized before inclusion in the analyses.
To measure partner relationship satisfaction, we used the 10-item Relationship Satisfaction (RS) scale (Røysamb, E, Vittersø, J, Tambs, K: In Progress, 2010) developed within MoBa, based on typical items used in previously developed scales [37, 38]. The RS scale has shown good psychometric properties, high structural and predictive validity, and correlates 0.92 with The Quality of Marriage Index . The scale contains 10 items, such as "I am satisfied with the relationship with my partner" and "My husband/partner and I have a close relationship". The response categories ranged from 1 (strongly agree) to 6 (strongly disagree). An index of overall relationship satisfaction based on 10 items was computed as an average score across items. Cronbach's alpha for the RS scale was 0.91.
The sociodemographic variables included total family income (measured using the combined income for the mother and father), maternal age, the mother's and father's educational level (six categories from public school to >4 years at university/college). Three mutually exclusive items measuring employment situation were included and entered as dummy variables (scored no = 0, yes = 1): unemployed (disability retirement or out of work), student/military and staying at home (working at home). Paid employment was the reference category. A dichotomous variable indicating single motherhood was also included in the analyses (scored 1 if they were both unmarried, did not live with a partner, and did not respond on any item of the RS scale).
Prior to conducting the multiple regression analyses, one-way analyses of variance (ANOVAs) were performed to test for curvilinear trends. A strong curvilinear effect was found for maternal age, in which teenage mothers were clearly more distressed, and a group from 20 to 24 years somewhat more distressed, than older mothers. After 24, there was no observed age gradient. Age was therefore entered as two dummy variables in the regression analyses: age younger than 20 years, and age 20-24 years. Age older than 24 years was the reference category.
Variables related to social network and support
Six items on type of household were collapsed into three dummy variables: living in a nuclear family, living with extended family, and living with others. Living alone was the reference category. Social support was measured by two items. The first question covered the number of supportive persons in addition to their partner: "Do you have anyone other than your husband/partner whom you can ask for advice in a difficult situation?" There were three response categories: "no", "yes 1-2 people", "yes more than 2 people". The second question measured the frequency of contact with extended family and friends: "How often do you meet or talk on the telephone with your family (other than those you live with) or close friends?" There were three response categories: "once per month or less", "2-8 times per month", and "more than twice a week". We also included one variable dealing with "housing situation". This was a dichotomous measure indicating whether the family lived in an apartment block versus in a house.
The somatic indicator was based on a 46 item checklist covering seven different groups of diseases: asthma/allergy/eczema, diabetes, cardiovascular disease/high blood pressure/hyperthyroidism/hypothyroidism, gastrointestinal disease, muscular/skeletal/articular disease, gynaecological/urinary/kidney disease, and "other disease". The respondents reported whether or not they had experienced problems in these areas before or during pregnancy.
Seven summative indices were created using the sum scores for each of the seven groups of diseases. The seven indices were entered into a regression analyses with maternal mental distress as a dependent variable. A general index based on the seven disease group scores was then generated to estimate the overall effect of somatic disease. The scores for each separate disease group were weighted by their respective regression coefficients estimated in the initial analyses and then summed. This procedure maximizes the predictive power of the global somatic indicator for mental health. Replacing the original seven somatic items with this index in the principal multivariate analysis of predictors of mental health essentially leaves the variance explained by somatic diseases unchanged. The purpose of collapsing these predictors was to obtain one single estimate of the total effect of all somatic diseases. The somatic disease indicator was standardized before inclusion in the analyses.
We included two dichotomous variables on the respondent's working hours: shift work and irregular work hours. Regular working hours was the reference category. In addition, information about present sick leave was included. Working conditions were measured by a 16 item scale used in previous studies . A factor analysis with an oblique rotation showed that a five-factor solution yielded well-defined dimensions. The dimensions were: work stress, physically demanding work, noisy work, lack of control and dissatisfaction at work. Five summative indices were created using these dimensions. Cronbach's alpha was 0.75 for work stress, 0.80 for physically demanding work, 0.80 for noisy work, 0.52 for lack of control and 0.69 for dissatisfaction at work.
One variable that specified the number of children without access to kindergarten was included. Frequency analyses showed that only 1% of the respondents had more than one child without access to kindergarten. Therefore, this variable was recoded into a dichotomous measure (0 or ≥1).
The questionnaire only included three types of life events, namely frequent moving, physical violence, and sexual pressure/violence. The moving item was treated as a continuous variable with five categories from 0 to ≥4.
Two variables covered current and previous experiences of violence, and both were measured using the following question, adapted from the Abuse Assessment Screen : "Have you ever in your adult life been slapped, hit, kicked, or bothered physically in any way?" Responses were categorized as 1 = no, 2 = do not remember, 3 = yes. "Current violence experience" was registered if the respondents had experienced violence during the current pregnancy, and "previous violence experience" if they had experienced violence during the six months preceding pregnancy. The last two variables about sexual pressure (referring to the last six months preceding pregnancy and the current pregnancy, respectively) asked whether the respondents had been coerced or forced to have sexual intercourse. The response categories were 1 = never, 2 = yes, coerced, 3 = yes, forced, 4 = yes, raped.
A dichotomous variable measuring smoking during the current pregnancy was included (smoking daily or sometimes = 1, never = 0).
Maternal alcohol problems
Two indices dealing with alcohol (ab)use were constructed. Five questions from Rutgers Alcohol Problems Index  were included in the questionnaire, and were used to construct a summative index for alcohol problems: "Have you ever experienced any of the following problems during the last year in relation to your alcohol consumption: 1) Argued with or had negative feelings for a family member; 2) suddenly found yourself somewhere without knowing how you got there; 3) Been absent from work or school; 4) Fainted or passed out suddenly; 5) Had a sad period". The response categories were 1 = never, 2 = once, 3 = several times. The variables were standardized before inclusion in the index. The general alcohol problem index was generated in order to estimate the overall effect of alcohol problems the last year.
A summative index measuring alcohol consumption during the last three months before pregnancy was calculated using four questions: "Did you drink 5 alcohol units at least once during the last 3 months before pregnancy?"; "How many units of alcohol do you usually drink when you consume alcohol?"; "How often did you consume alcohol in the 3 months before you became pregnant?"; "How many units of alcohol do you have to drink before you feel any effect?" (rated on Likert-type scales). The first three questions were derived from The Alcohol Use Disorders Identification Test  and modified for use in MoBa. Cronbach's alpha was 0.53 for the alcohol problems-scale, and 0.69 for the alcohol consumption scale.
Information on history of depression was obtained using an index based on DSM-III criteria developed by Kendler . This index contained five questions about symptoms of depression. The respondents reported whether they had ever experienced any of the five types of depressive symptoms lasting at least two weeks, and whether three or more symptoms had been present simultaneously. An ordinal measure was generated in which the response categories ranged from 0 (0 or 1 depressive symptom) to 4 (5 symptoms, at least 3 at the same time).
Treatment of missing values
Including participants for whom data are partially missing, increases the power of the analyses. In general, the missing rates were low. For the continuous variables consisting of single items, the mean proportion of missing values was 3.3%, ranging from 0.5% to 5.9%. A substantial proportion of the mothers were not employed, and some employed mothers did not complete all items on working conditions, giving rates of missing data ranging from 11.1% to 15.7% on the five indices of working conditions. For the other variables used in the analyses, the frequency of missing values varied between 0% and 10.9% with an average of 3.6%. Maternal alcohol consumption, sexual pressure and violence experiences were the variables with highest missing rates.
We used SPSS MVA, Expectation Maximization  to impute values for missing scores on the continuously distributed SCL-5 and RS scales. Imputed values were generated when respondents already had reported values for more than half of the items on SCL-5, and at least half of the items on the RS scale. For single mothers, we carried out a mean substitution for the "overall" RS score.
For variables not included as items in a psychometric instrument, or where highly correlated variables suitable for predictive imputation were not available, missing values were replaced by sample means. Missing data on the indices measuring working conditions were substituted by sample mean values. In addition, we created two dummy variables, one indicating a moderate number (1-2) of missing values on the working condition items and one indicating a high number (3-5) of missing values. These variables tested whether women with incomplete data on working conditions (unemployed women and the incomplete responders), deviated from the remaining sample regarding mental distress. Missing values on the alcohol consumption and alcohol problem indices were replaced by sample means.
For the social support variables, we replaced missing values with the median category. The missing value for "housing situation" was replaced with a score of 1, indicating that the family lived in an apartment block.
Non-response on income and education may be highly non-random in terms of an upwards selection, therefore mean substitution may not be very suitable. We used maternal age and maternal and paternal income and education, which are all inter-correlated, to calculate suitable constants by which missing values were replaced. For instance mothers with missing values on income on average reported lower values than sample means on maternal age and education and paternal income and education. These mean values for income non-responders compared to the mean values for income responders were used to calculate the most suitable constant for replacing missing maternal income. For single mothers, we replaced a missing paternal income with zero. Child maintenance from the father was already included in single mothers' reported income. After replacement of missing values all but 2133 cases (4.1%) had complete data on all variables included in the analyses, resulting in a net sample size of 49,425.
The 37 selected predictors of maternal emotional distress (besides of the two dummy variables indicating missing values) were examined by using multiple regression analyses. Preliminary one-way ANOVAs were used to test for possible curvilinear trends. Whenever nonlinear trends between predictor variables and emotional distress were detected, the predictor was grouped and entered into the regression analysis as two or more dummy variables. Interaction effects were tested in separate regression analyses together with all the predictors, one interaction term at a time.
We did not enter lifetime depression in the main analyses, due to high overlap with the dependent variable. Adjusting for this variable, which could be considered a "baseline" measure, could skew the scope of the study toward examining change in mental health as a result of factors related to pregnancy. Nevertheless, associations between history of depression and pregnancy-related and postpartum depression have been established in other studies [46–48]. Therefore, we conducted supplementary regression analyses in which lifetime depression was entered together with all the other variables, to measure the effect on maternal emotional distress.
Effect of independent variables
Prior to the multivariate analyses we examined the statistical relationships between all explanatory variables. In total, three correlations exceeded 0.40, those between living with "other persons" and living in an extended family (r = 0.83), being single and living in a nuclear family (r = -0.44), and mother's and father's education (r = 0.42). Twelve other correlations reached values higher than 0.30. Of special interest were possible confounding between relationship satisfaction and the remaining variables. Four variables, number of supportive persons (in addition to the partner), dissatisfaction at work, maternal alcohol problems, and living in a nuclear family, correlated with absolute values ranging from 0.10 - 0.15. All other associations between the relationship satisfaction and the other explanatory variables were weaker than 0.10.
Effect of various risk factors on the level of maternal emotional distress (scl-5 score) in gestational week 17 among 49,425 pregnant women.
Maternal age (< 20)
Maternal age (20-24)
Social network and family
Number of supportive persons
Contact frequency (family/friends)
Dissatisfaction at work
Lacking control over work situation
Irregular working hours
Mother on sick leave
Children without kindergarten
Previous violence experience
Current violence experience
Previous sexual pressure
Health and lifestyle
Maternal alcohol problems last year
Of the 37 explanatory variables included in the analyses, relationship dissatisfaction had the strongest unique effect on maternal emotional distress (β = 0.25). Dissatisfaction at work (β = 0.11), somatic disease (β = 0.11), work stress (β = 0.10) and maternal alcohol problems in the last year (β = 0.09) were also among the strongest risk factors in the analyses.
There were few single mothers in the study sample, preventing a high β for being single mother. However, the adjusted increase in SCL scores for single mothers as compared to the remaining sample was 0.43 standard deviations. This means that being a single mother increases the risk for maternal emotional distress in pregnancy. Previous sexual pressure also had a considerable effect (b = 0.25) for the relatively few (n = 452) women who reported some degree of sexual pressure. Of those, 407 reported being coerced, 19 reported being forced and 26 women reported being raped. Comparing the groups with highest and lowest scores, the SCL-5 score was 0.75 standard deviations higher in the group with highest degree of previous sexual pressure. A strong curvilinear effect was found for mother's age. The adjusted deviations (b) were 0.21 (P < 0.001) for age younger than 20 years, and 0.06 (P < 0.001) for age 20-24 years. This means that younger age is an important risk factor for maternal emotional distress during pregnancy.
The following factors did not have unique significant effects on maternal emotional distress (all with P > 0.01): mother staying at home, physically demanding work, father student/military, father staying at home, living with extended family, living with others, alcohol consumption, and current sexual pressure, which given the large sample size implies that the effects are only minimally different from zero.
A significant but small effect, b = 0.07, of the dummy variable indicating "missing data on 3-5 working condition items" is not tabulated. The effect of the dummy variable indicating 1-2 blank working condition items did not reach significance.
Model with lifetime depression as a risk factor
Information on history of depression was entered together with the variables included in the analysis of main effects. Lifetime depression was a stronger predictor of emotional distress than any other variable (β = 0.27, b = 0.21, P < 0.001). Relationship dissatisfaction was the second strongest predictor of maternal emotional distress in this model (β = 0.21, b = 0.33, P < 0.001). Thus, even with lifetime depression included in the analyses, the effect of relationship satisfaction remained strong. We also found that 23 of the other originally significant predictors (all but mothers' education, lacking control over work situation, and contact frequency) still had a significant effect (P < 0.001) on emotional distress.
Interaction effects between relationship satisfaction and 10 predictors on maternal emotional distress; main effects (b) for various strata with low or high relationship satisfaction.
Low (lower 10%)
Moderately high (29%)
High (upper 38%)
Significant interaction effects (P < 0.05) were found between relationship satisfaction and the following eight predictors: dissatisfaction at work, work stress, somatic disease, maternal smoking, low family income, irregular working hours, mother on sick leave and frequent moving. In general, the results indicated that high relationship satisfaction protects against the negative effects of these eight risk factors.
To our knowledge, this is the first study to analyse risk factors for maternal emotional distress in a large cohort of pregnant women. In the current study including 49,425 pregnant women in Norway, 26 of the 37 predictors evaluated had a significant unique effect on maternal emotional distress. Relationship dissatisfaction, dissatisfaction at work, work stress, somatic disease and alcohol problems during the preceding year were among the strongest predictors. Relationship dissatisfaction had the strongest effect and explained 6.3% of the total variance. The results also show that a good relationship with partner may act as a protective factor against some stressors.
Our observation of a strong association between partner relationship and emotional distress is consistent with previous results regarding mental distress, anxiety and depression and with our main hypothesis. Partner relationship quality has been shown to be significantly associated with women's mental health [49, 50] and with major depression [51–53] in general, and during pregnancy [6, 12, 19, 54]. It is noteworthy that some studies [12, 55] differentiate between partner support and relationship satisfaction and investigate the effect of each factors. For example, O'Hara (1986) found that women who experience depression during pregnancy reported less support from their spouses than did non-depressed women. They did not, however, differ from non-depressed subjects with regard to level of marital satisfaction, which according to the authors could be considered a broader phenomenon than partner support . The differences and association between these concepts remain unclear. Relationship satisfaction and partner support are measured in different and sometimes overlapping ways in the various studies, making it difficult to compare the findings. Still, our results seem to be in line with previous results regarding the significance of partner relationship quality in pregnancy.
Most of the previous studies suffered from small sample sizes. One notable exception is a Swedish study of 3011 pregnant women , which showed that lack of support from the partner was the most important risk factor for depressive mood. However, partner support was measured with only one item. Our more comprehensive measure of partner relationship satisfaction, our large variety of covariates, and our large sample size ensure greater applicability of the results and more precise effect estimates than did the Swedish study.
Our findings can be interpreted in several ways. One explanation for the importance of relationship satisfaction in pregnancy may be associated with the mothers' particular vulnerability and need for support during this time. The results from one study showed that the lack of a cohabiting partner was a significant risk factor for depression during pregnancy, but not postpartum . The transition to parenthood can be a critical phase and a time when a woman may benefit the most from partner support. A pregnant woman must not only carry the baby to term safely, but also accept the sacrifices that motherhood demands. She must ensure the acceptance of the child by the family, develop an attachment to the baby within, and prepare for the birth. She must also adjust to the alteration in her physical appearance and develop a somewhat different relationship with the father of the child. However, studies of depression postpartum have also found an association between depression and having no partner [56, 57], or experiencing a low relationship satisfaction [56, 58].
Having a child is a mutual project for the couple. Previous research has shown that most pregnant women receive their primary social support from their partners and their own mothers [59, 60]. Other studies have demonstrated that the single most important source of social support for expectant mothers is their partners . Hobfoll (1986) demonstrated that social support could be gleaned from other sources, but that partner support was especially critical during pregnancy and delivery . This could explain the strong negative effect of single motherhood observed in the current study.
Results from a study of Mexican immigrant women in Los Angeles suggested that spousal support might not have the same significance for all cultural groups. These women experienced less prenatal and postnatal anxiety if they received support from friends and family, but there was no evidence of a relationship between anxiety and lack of support from the spouse . The strong effect of partner relationship observed in the current study probably reflects the somewhat weaker position of extended families and the somewhat stronger position of nuclear families in Norway than in most other countries. However, an association between partner relationship quality and depression in the postpartum period is demonstrated in Asian cultures as well .
In cross-sectional studies like ours, any conclusions drawn about causal direction are tentative. Thus, it could be that high levels of maternal emotional distress contribute to relationship problems. Previous studies reported that relative to partners of non-distressed women, partners of distressed women reported significant reductions in the partnership quality during pregnancy and postpartum. They also had higher levels of anxiety and anger .
Another striking finding was that the respondents' working conditions seemed to be important for emotional distress during early pregnancy. Dissatisfaction at work and work stress were the second and fourth strongest predictors of emotional distress in our sample. Research has demonstrated that working conditions in pregnancy may affect pregnancy outcome . To our knowledge, no previous studies have examined specific aspects of women's work situation as possible risk factors for emotional distress in pregnancy. Studies from the general population have demonstrated that the risk of depressive and anxiety disorders increases with various work characteristics, such as a high level of psychological demands, effort-reward imbalance, low decision authority at work, low job control, high job strain, and low support [66–70].
Working can be both advantageous and detrimental for mental health [69, 71]. Plaisier et al. found that having a job protected against anxiety and depression for men and women without children but not for women with children . Women with young children might be more susceptible to the stresses of juggling the demands of multiple roles, such as worker and parent, which could be detrimental to mental health. In our sample, 49.8% of the women had children and were also working or studying. One possible explanation for the strong effect of work-related variables is that work dissatisfaction and work stress come in addition to the existing stress of multiple roles for a large number of the respondents.
Our findings indicate that somatic disease either before or during pregnancy had a considerable negative effect on maternal emotional distress in pregnancy. This is in line with previous research demonstrating that prenatal depression and anxiety is associated with more frequent somatic symptoms [73, 74]. An association between maternal somatic health and depression has also been shown in the postpartum period , and among mothers of toddlers and pre-school children .
Alcohol disorders have often been reported to be a risk factor for depressive disorders . However, in a recent study based on a Swedish community sample, alcohol disorders represented a risk factor only for males . Alcohol consumption has been clearly associated with adverse/severe and sometimes long-lasting consequences for the child, even when consumed in small to moderate quantities during pregnancy . Therefore, alcohol problems might affect mental health among pregnant women even stronger than among women in general. The results from the current study showed that having alcohol problems during the year preceding pregnancy was a significant risk factor for maternal emotional distress during pregnancy. To our knowledge, only a few studies have examined the effect of maternal alcohol problems on emotional distress in pregnant women. One Finnish study showed a significant association (OR = 3.4, P < 0.001) between substance dependency and maternal depression in a sample of 391 women who were 14-37 weeks pregnant .
Previous sexual pressure was reported by few women in our sample but showed a considerable effect for the women affected. Comparing the groups with highest and lowest scores, the SCL-5 score was 0.75 standard deviations higher in the group with the highest degree of previous sexual pressure as compared to the women who reported no sexual pressure. In contrast, a previous Norwegian study assessed depression in 2730 post-partum and non-postpartum women, and found no evidence of increased depression scores among women having been pressed or forced to intercourse. This was the case for both postpartum and non-postpartum women . Under-reporting of such experiences might hinder detection of risk effects in any but very large samples.
Being a single mother increased the risk for emotional distress in pregnancy. The Scandinavian countries are characterised by reasonable social benefit for lone mothers, long term paid parental leave and good access to childcare, which are all important factors for parent's well-being , and maybe single parents in particular. Nevertheless, being single seems to represent a considerable strain for pregnant women.
Also noteworthy is the absence of effects from certain factors, such as alcohol consumption. Some previous studies have investigated the effect of alcohol use on depression in pregnancy, and the findings are inconsistent . The results from the current study show that alcohol problems have a significant unique effect on emotional distress, while alcohol consumption has not. Given the large sample size of this study, the absence of effects is informative.
The interaction between mental health, social network and stress is complex. In accordance with our hypothesis, relationship satisfaction seemed to act as a buffer [24, 26] for some risk factors, like work stress, dissatisfaction at work, and frequent moving. When women reported having a good relationship, they seemed better able to cope with such strains without experiencing increased emotional distress. To our knowledge, only a few studies have investigated interaction effects between relationship satisfaction and other factors on maternal emotional distress in pregnancy. One study examined the effect of life stress and social support (from partner, relatives and friends) on anxiety in a sample of 190 low-income women. In addition to the main effects of social support, their findings indicated a significant stress-buffering effect from social support . Results from the current study further contribute to this body of evidence by demonstrating the buffering effects of relationship satisfaction.
Strengths and limitations
High statistical power and precise estimates are the most important strengths of this study. Small effects and even negative results are still highly informative due to the narrow confidence intervals. The large number and variety of predictor variables are also important advantages.
Nonetheless, our findings must be interpreted carefully due to several limitations. First, in cross-sectional studies, the data are not informative regarding causal directions. Although we find it likely that a good partner relationship protects against poor mental health, we cannot rule out the reverse causal pathway . Second, there may be response biases that cause spurious correlations between self-reported predictor and outcome variables. Third, the validity and reliability of a brief self-report scale such as the current outcome measure might be less than optimal. However, a reasonably good validity was demonstrated in a recent study, comparing a dichotomised SCL-5 with an "any disorder" variable based on the Composite International Diagnostic Interview CIDI . This variable was scored '1' if any anxiety or depression disorders were present, else '0'. Furthermore, the results indicated that all this statistical correspondence was due to genes that coded both for the SCL scores and for the internalizing disorders measured with the CIDI . The first and second limitation could have led to inflated estimates, whereas the third could have deflated them. Fourth, 43.8% of the invited women completed the first questionnaire. Although this response rate is low, it is not uncommon in large epidemiologic studies and does not necessarily imply a biased sample . In addition, while preventing reliable estimation of occurrence of mental health problems, a moderate sample selection is not expected to affect results from analytic epidemiology dramatically . Significant mean differences in prevalence estimates between the cohort participants and the total population have been found for certain variables. Despite this, no statistically significant differences in exposure-outcome associations are found . This indicates there is little reason to consider the selection bias a threat to the generalizability of our results showing associations between variables, like relationship satisfaction and emotional distress.
Our findings demonstrate the importance of partner relationship quality, working conditions, alcohol problems, and somatic disease as predictors of maternal emotional distress in early pregnancy. Even though perinatal depression is a well known clinical phenomenon, women at risk are rarely recognised by health professionals [6, 47, 84]. Traditionally, medical and midwife practitioners have focused on the physical health of the mother and the foetus. Considerably less attention has been given to emotional and psychological issues . The mental health of the mother is important not only for herself, but also for the physical and psychological health of her children and the welfare of the family. Hence, failure to recognize and assist women who suffer from emotional distress during pregnancy is failure to address a major public health problem .
Our results suggest a need for a more comprehensive antenatal program which focuses on the foetus' development, the woman's somatic health, as well as the woman's mental well- being. The importance of a good partner relationship that consists of both emotional and practical support should be highlighted to all expecting couples. Many expecting couples participate in courses that prepare them for the delivery. These courses could therefore be extended to include topics and exercises that strengthen positive aspects of their relationship. All signs of trouble in a woman's adaptation to pregnancy should be taken seriously by obstetricians, nurse midwives, and mental health professionals. Special attention needs to be paid to the woman's relationship with her partner. Early intervention that involves both the woman and her partner may be successfully initiated in some cases to strengthen the foundation for the family's future development.
Relationship dissatisfaction was clearly associated with maternal emotional distress, and relationship satisfaction appeared protective in the presence of certain stressful events. Thus, some types of stress will probably be tolerable for women who experience a good and close relationship with their partners. Working conditions, somatic diseases, and alcohol problems should also be taken into consideration. From a prevention point of view, it is important to pay attention to women who appear to lack the protection from a good partner relationship and who simultaneously experience several risk factors.
The Norwegian Mother and Child Cohort Study is supported by the Norwegian Ministry of Health, NIH/NIEHS (grant no N01-ES-85433), NIH/NINDS (grant no.1 UO1 NS 047537-01), and the Norwegian Research Council/FUGE (grant no.151918/S10). Our study is supported by the Norwegian Foundation for Health and Rehabilitation through The Norwegian Council for Mental Health.
- Bennett HA, Einarson A, Taddio A, Koren G, Einarson TR: Depression during Pregnancy: Overview of Clinical Factors. Clin Drug Invest. 2004, 24: 157-179. 10.2165/00044011-200424030-00004.View ArticleGoogle Scholar
- Bennett HA, Einarson A, Taddio A, Koren G, Einarson TR: Prevalence of depression during pregnancy: systematic review. Obstet Gynecol. 2004, 103: 698-709. 10.1097/01.AOG.0000116689.75396.5f.View ArticlePubMedGoogle Scholar
- Stern DN: The Motherhood Constellation. 1995, New York: Basic BooksGoogle Scholar
- Eberhard-Gran M, Tambs K, Opjordsmoen S, Skrondal A, Eskild A: Depression during pregnancy and after delivery: a repeated measurement study. J Psychosom Obstet Gynaecol. 2004, 25: 15-21. 10.1080/01674820410001737405.View ArticlePubMedGoogle Scholar
- Evans J, Heron J, Francomb H, Oke S, Golding J: Cohort study of depressed mood during pregnancy and after childbirth. BMJ. 2001, 323: 257-260. 10.1136/bmj.323.7307.257.View ArticlePubMedPubMed CentralGoogle Scholar
- Johanson R, Chapman G, Murray D, Johnson I, Cox J: The North Staffordshire Maternity Hospital prospective study of pregnancy-associated depression. J Psychosom Obstet Gynecol. 2000, 21: 93-97. 10.3109/01674820009075614.View ArticleGoogle Scholar
- Talge NM, Neal C, Glover V, Early Stress, Translational Research and Prevention Science Network: Fetal and Neonatal Experience on Child and Adolescent Mental Health: Antenatal maternal stress and long-term effects on child neurodevelopment: how and why?. J Child Psychol Psychiatry. 2007, 48: 245-261. 10.1111/j.1469-7610.2006.01714.x.View ArticlePubMedGoogle Scholar
- Milgrom J, Gemmill AW, Bilszta JL, Hayes B, Barnett B, Brooks J, Ericksen J, Ellwood D, Buist A: Antenatal risk factors for postnatal depression: a large prospective study. J Affect Disord. 2008, 108: 147-157. 10.1016/j.jad.2007.10.014.View ArticlePubMedGoogle Scholar
- Ystrom E, Niegel S, Klepp KI, Vollrath ME: The impact of maternal negative affectivity and general self-efficacy on breastfeeding: the Norwegian Mother and Child Cohort Study. J Pediatr. 2008, 152: 68-72. 10.1016/j.jpeds.2007.06.005.View ArticlePubMedGoogle Scholar
- Luoma I, Tamminen T, Kaukonen P, Laippala P, Puura K, Salmelin R, Almquist F: Longitudinal study of maternal depressive symptoms and child well-being. J Am Acad Child Adolesc Psychiatry. 2001, 40: 1367-1374. 10.1097/00004583-200112000-00006.View ArticlePubMedGoogle Scholar
- Lancaster CA, Gold KJ, Flynn HA, Yoo H, Marcus SM, Davis MM: Risk factors for depressive symptoms during pregnancy: a systematic review. Am J Obstet Gynecol. 2010, 202: 5-14. 10.1016/j.ajog.2009.09.007.View ArticlePubMedPubMed CentralGoogle Scholar
- Morse CA, Buist A, Durkin S: First-time parenthood: influences on pre- and postnatal adjustment in fathers and mothers. J Psychosom Obstet Gynecol. 2000, 21: 109-120. 10.3109/01674820009075616.View ArticleGoogle Scholar
- Norbeck JS, Anderson NJ: Life stress, social support, and anxiety in mid- and late-pregnancy among low income women. Res Nurs Health. 1989, 12: 281-287. 10.1002/nur.4770120503.View ArticlePubMedGoogle Scholar
- Witt WP, DeLeire T, Hagen EW, Wichmann MA, Wisk LE, Spear HA, Cheng ER, Maddox T, Hampton J: The prevalence and determinants of antepartum mental health problems among women in the USA: a nationally representative population-based study. Arch Wom Ment Health. 2010, 13: 425-437. 10.1007/s00737-010-0176-0.View ArticleGoogle Scholar
- Hobfoll SE, Ritter C, Lavin J, Hulsizer MR, Cameron RP: Depression prevalence and incidence among inner-city pregnant and postpartum women. J Consult Clin Psychol. 1995, 63: 445-453. 10.1037/0022-006X.63.3.445.View ArticlePubMedGoogle Scholar
- Rich-Edwards JW, Kleinman K, Abrams A, Harlow BL, Mc Laughlin TJ, Joffe H, Gillman MW: Sociodemographic predictors of antenatal and postpartum depressive symptoms among women in a medical group practice. J Epidemiol Community Health. 2006, 60: 221-227. 10.1136/jech.2005.039370.View ArticlePubMedPubMed CentralGoogle Scholar
- Melville JL, Gavin A, Guo Y, Fan MY, Katon WJ: Depressive disorders during pregnancy: prevalence and risk factors in a large urban sample. Obstet Gynecol. 2010, 116: 1064-1070. 10.1097/AOG.0b013e3181f60b0a.View ArticlePubMedPubMed CentralGoogle Scholar
- Gotlib IH, Whiffen VE, Mount JH, Milne K, Cordy NI: Prevalence rates and demographic characteristics associated with depression in pregnancy and the postpartum. J Consult Clin Psychol. 1989, 57: 269-274. 10.1037/0022-006X.57.2.269.View ArticlePubMedGoogle Scholar
- Kitamura T, Shima S, Sugawara M, Toda MA: Clinical and psychosocial correlates of antenatal depression: a review. Psychother Psychosom. 1996, 65: 117-123. 10.1159/000289062.View ArticlePubMedGoogle Scholar
- Pereira PK, Lovisi GM, Pilowsky DL, Lima LA, Legay LF: Depression during pregnancy: prevalence and risk factors among women attending a public health clinic in Rio de Janeiro, Brazil. Cad Saude Publica. 2009, 25: 2725-2736.PubMedGoogle Scholar
- Bottomley KL, Lancaster SJ: The association between depressive symptoms and smoking in pregnant adolescents. Psychol Health Med. 2008, 13: 574-582. 10.1080/13548500801927121.View ArticlePubMedGoogle Scholar
- Jomeen J, Martin CR: Assessment and relationship of sleep quality to depression in early pregnancy. J Reprod Infant Psychol. 2007, 25: 87-99. 10.1080/02646830601117308.View ArticleGoogle Scholar
- Rubertsson C, Waldenström U, Wickberg B: Depressive mood in early pregnancy: prevalence and women at risk in a national Swedish sample. J Reprod Infant Psychol. 2003, 21: 113-123. 10.1080/0264683031000124073.View ArticleGoogle Scholar
- Cohen S, Wills TA: Stress, social support, and the buffering hypothesis. Psychol Bull. 1985, 98: 310-357. 10.1037/0033-2909.98.2.310.View ArticlePubMedGoogle Scholar
- Cooke BD, Rossman MM, McCubbin HI, Pattersson JM: Examining the Definition and Assessment of Social Support: A Resource for Individuals and Families. Family Relations. 1988, 37: 211-216. 10.2307/584322.View ArticleGoogle Scholar
- Dalgard OS, Bjork S, Tambs K: Social support, negative life events and mental health. Br J Psychiatry. 1995, 166: 29-34. 10.1192/bjp.166.1.29.View ArticlePubMedGoogle Scholar
- Olstad R, Sexton H, Sogaard AJ: The Finnmark Study. A prospective population study of the social support buffer hypothesis, specific stressors and mental distress. Soc Psychiatry Psychiatr Epidemiol. 2001, 36: 582-589. 10.1007/s127-001-8197-0.View ArticlePubMedGoogle Scholar
- Magnus P, Irgens LM, Haug K, Nystad W, Skjaerven R, Stoltenberg C, MoBa Study Group: Cohort profile: the Norwegian Mother and Child Cohort Study (MoBa). Int J Epidemiol. 2006, 35: 1146-1150. 10.1093/ije/dyl170.View ArticlePubMedGoogle Scholar
- Nilsen RM, Vollset SE, Gjessing HK, Skjaerven R, Melve KK, Schreuder P, Alsaker ER, Haug K, Daltveit AK, Magnus P: Self-selection and bias in a large prospective pregnancy cohort in Norway. Paediatr Perinat Epidemiol. 2009, 23: 597-608. 10.1111/j.1365-3016.2009.01062.x.View ArticlePubMedGoogle Scholar
- Bulik CM, Von Holle A, Hamer R, Knoph Berg C, Torgersen L, Magnus P, Stoltenberg C, Siega-Riz AM, Sullivan P, Reichborn-Kjennerud T: Patterns of remission, continuation and incidence of broadly defined eating disorders during early pregnancy in the Norwegian Mother and Child Cohort Study (MoBa). Psychol Med. 2007, 37: 1109-1118. 10.1017/S0033291707000724.View ArticlePubMedPubMed CentralGoogle Scholar
- Statistics Norway 2010. [http://tinyurl.com/32wwx5h]
- Medical Birth Registry of Norway 2010. [http://statbank.ssb.no/statistikkbanken/]
- Winokur A, Winokur DF, Rickels K, Cox DS: Symptoms of emotional distress in a family planning service: stability over a four-week period. Br J Psychiatry. 1984, 144: 395-399. 10.1192/bjp.144.4.395.View ArticlePubMedGoogle Scholar
- Strand BH, Dalgard OS, Tambs K, Rognerud M: Measuring the mental health status of the Norwegian population: a comparison of the instruments SCL-25, SCL-10, SCL-5 and MHI-5 (SF-36). Nordic Journal of Psychiatry. 2003, 57: 113-118. 10.1080/08039480310000932.View ArticlePubMedGoogle Scholar
- Tambs K, Moum T: How well can a few questionnaire items indicate anxiety and depression?. Acta Psychiatr Scand. 1993, 87: 364-367. 10.1111/j.1600-0447.1993.tb03388.x.View ArticlePubMedGoogle Scholar
- Nes RB, Roysamb E, Reichborn-Kjennerud T, Harris JR, Tambs K: Symptoms of anxiety and depression in young adults: genetic and environmental influences on stability and change. Twin Res Hum Genet: Journal of International Society for Twin Studies. 2007, 10: 450-461. 10.1375/twin.10.3.450.View ArticleGoogle Scholar
- Blum J, Mehrabian A: Personality and Temperament Correlates of Marital Satisfaction. J Pers. 1999, 67: 93-125. 10.1111/1467-6494.00049.View ArticleGoogle Scholar
- Hendrick SS: A Generic Measure of Relationship Satisfaction. J Marr Fam. 1988, 50: 93-98. 10.2307/352430.View ArticleGoogle Scholar
- Norton R: Measuring marital quality: A critical look at the dependent variable. J Marr Fam. 1983, 45: 141-151. 10.2307/351302.View ArticleGoogle Scholar
- Kristensen P, Nordhagen R, Wergeland E, Bjerkedal T: Job adjustment and absence from work in mid-pregnancy in the Norwegian Mother and Child Cohort Study (MoBa). Occup Environ Med. 2008, 65: 560-566. 10.1136/oem.2007.035626.View ArticlePubMedGoogle Scholar
- McFarlane J, Parker B, Soeken K, Bullock L: Assessing for abuse during pregnancy. Severity and frequency of injuries and associated entry into prenatal care. JAMA. 1992, 267: 3176-3178. 10.1001/jama.267.23.3176.View ArticlePubMedGoogle Scholar
- White HR, Labouvie EW: Towards the assessment of adolescent problem drinking. J Stud Alcohol. 1989, stud: 30-37.View ArticleGoogle Scholar
- Saunders JB, Aasland OG, Babor TF, De la Fuente JR, Grant M: Development of the Alcohol Use Disorders Identification Test (AUDIT): WHO Collaborative Project on Early Detection of Persons with Harmful Alcohol Consumption--II. Addiction. 1993, 88: 791-804. 10.1111/j.1360-0443.1993.tb02093.x.View ArticlePubMedGoogle Scholar
- Kendler KS, Neale MC, Kessler RC, Heath AC, Eaves LJ: The lifetime history of major depression in women. Reliability of diagnosis and heritability. Arch Gen Psychiatry. 1993, 50: 863-870.View ArticlePubMedGoogle Scholar
- Graham JW, Hofer SM, MacKinnon DP: Maximizing the Usefulness of Data Obtained with Planned Missing Value Patterns: An Application of Maximum Likelihood Procedures. Multivariate Behav Res. 1996, 31: 197-218. 10.1207/s15327906mbr3102_3.View ArticlePubMedGoogle Scholar
- Eberhard-Gran M, Eskild A, Tambs K, Samuelsen SO, Opjordsmoen S: Depression in postpartum and non-postpartum women: prevalence and risk factors. Acta Psychiatr Scand. 2002, 106: 426-433. 10.1034/j.1600-0447.2002.02408.x.View ArticlePubMedGoogle Scholar
- Nielsen FD, Videbech P, Hedegaard M, Dalby Salvig J, Secher NJ: Postpartum depression: identification of women at risk. BJOG: An International Journal of Obstetrics and Gynaecology. 2000, 107: 1210-1217. 10.1111/j.1471-0528.2000.tb11609.x.View ArticleGoogle Scholar
- O'Hara MW, Neunaber DJ, Zekoski EM: Prospective study of postpartum depression: prevalence, course, and predictive factors. J Abnorm Psychol. 1984, 93: 158-171.View ArticlePubMedGoogle Scholar
- DeLongis A, Capreol M, Holtzman S, O'Brien T, Campbell J: Social support and social strain among husbands and wives: a multilevel analysis. J Fam Psychol. 2004, 18: 470-479. 10.1037/0893-3220.127.116.110.View ArticlePubMedGoogle Scholar
- Spotts EL, Neiderhiser JM, Ganiban J, Reiss D, Lichtenstein P, Hansson K, Cederblad M, Pedersen NL: Accounting for depressive symptoms in women: a twin study of associations with interpersonal relationships. J Affect Disord. 2004, 82: 101-111. 10.1016/j.jad.2003.10.005.View ArticlePubMedGoogle Scholar
- Zlotnick C, Kohn R, Keitner G, DellaGrotta SA: The relationship between quality of interpersonal relationships and major depressive disorder: findings from the National Comorbidity Survey. J Affect Disord. 2000, 59: 205-215. 10.1016/S0165-0327(99)00153-6.View ArticlePubMedGoogle Scholar
- Whisman MA: Marital dissatisfaction and psychiatric disorders: results from the National Comorbidity Survey. J Abnorm Psychol. 1999, 108: 701-706. 10.1037/0021-843X.108.4.701.View ArticlePubMedGoogle Scholar
- Hammen C: Interpersonal stress and depression in women. J Affect Disord. 2003, 74: 49-57. 10.1016/S0165-0327(02)00430-5.View ArticlePubMedGoogle Scholar
- Kumar R, Robson KM: A prospective study of emotional disorders in childbearing women. Br J Psychiatry. 1984, 144: 35-47. 10.1192/bjp.144.1.35.View ArticlePubMedGoogle Scholar
- O'Hara MW: Social support, life events, and depression during pregnancy and the puerperium. Arch Gen Psychiatry. 1986, 43: 569-573.View ArticlePubMedGoogle Scholar
- Beck CT: Predictors of postpartum depression: an update. Nurs Res. 2001, 50: 275-285. 10.1097/00006199-200109000-00004.View ArticlePubMedGoogle Scholar
- Beck CT: Revision of the Postpartum Depression Predictors Inventory. J Obstet Gynecol Neonatal Nurs. 2001, 31: 394-402.View ArticleGoogle Scholar
- Bernazzani O, Saucier JF, David H, Borgeat F: Psychosocial predictors of depressive symptomatology level in postpartum women. J Affect Disord. 1997, 46: 39-49. 10.1016/S0165-0327(97)00077-3.View ArticlePubMedGoogle Scholar
- Chalmers B, Meyer D: Companionship in the perinatal period. A cross-cultural survey of women's experiences. J Nurse Midwifery. 1994, 39: 265-272. 10.1016/0091-2182(94)90031-0.View ArticlePubMedGoogle Scholar
- Logsdon MC, Birkimer JC, Barbee AP: Social Support Providers for Postpartum Women. J Soc Beh Pers. 1997, 12: 89-102.Google Scholar
- Brown MA: Social support during pregnancy: a unidimensional or multidimensional construct?. Nurs Res. 1986, 35: 4-9. 10.1097/00006199-198601000-00002.View ArticlePubMedGoogle Scholar
- Hobfoll SE: Social Support: Research, Theory, and Applications from Research on Women. Stress, Social Support, and Women. Edited by: Hobfoll, SE. 1986, Washington D.C: Hemisphere, 239-256.Google Scholar
- Engle PL, Scrimshaw SC, Zambrana RE, Dunkel-Schetter C: Prenatal and postnatal anxiety in Mexican women giving birth in Los Angeles. Health Psychol. 1990, 9: 285-299. 10.1037/0278-618.104.22.1685.View ArticlePubMedGoogle Scholar
- Klainin P, Arthur DG: Postpartum depression in Asian cultures: a literature review. Int J Nurs Stud. 2009, 46: 1355-1373. 10.1016/j.ijnurstu.2009.02.012.View ArticlePubMedGoogle Scholar
- Ahlborg G: Physical work load and pregnancy outcome. J Occup Environ Med. 1995, 37: 941-944. 10.1097/00043764-199508000-00009.View ArticlePubMedGoogle Scholar
- Andrea H, Bultmann U, Beurskens AJ, Swaen GM, van Schayck CP, Kant IJ: Anxiety and depression in the working population using the HAD Scale--psychometrics, prevalence and relationships with psychosocial work characteristics. Soc Psychiatry Psychiatr Epidemiol. 2004, 39: 637-646. 10.1007/s00127-004-0797-6.View ArticlePubMedGoogle Scholar
- Plaisier I, de Bruijn JG, de Graaf R, ten Have M, Beekman AT, Penninx BW: The contribution of working conditions and social support to the onset of depressive and anxiety disorders among male and female employees. Soc Sci Med. 2007, 64: 401-410. 10.1016/j.socscimed.2006.09.008.View ArticlePubMedGoogle Scholar
- Sanne B, Mykletun A, Dahl AA, Moen BE, Tell GS: Testing the Job Demand-Control-Support model with anxiety and depression as outcomes: the Hordaland Health Study. Occ Med (Oxford). 2005, 55: 463-473. 10.1093/occmed/kqi071.View ArticleGoogle Scholar
- Stansfeld SA, Fuhrer R, Shipley MJ, Marmot MG: Work characteristics predict psychiatric disorder: prospective results from the Whitehall II Study. Occup Environ Med. 1999, 56: 302-307. 10.1136/oem.56.5.302.View ArticlePubMedPubMed CentralGoogle Scholar
- Virtanen M, Honkonen T, Kivimaki M, Ahola K, Vahtera J, Aromaa A, Lonnquist J: Work stress, mental health and antidepressant medication findings from the Health 2000 Study. J Affect Disord. 2007, 98: 189-197. 10.1016/j.jad.2006.05.034.View ArticlePubMedGoogle Scholar
- Iacovides A, Fountoulakis KN, Kaprinis S, Kaprinis G: The relationship between job stress, burnout and clinical depression. J Affect Disord. 2003, 75: 209-221. 10.1016/S0165-0327(02)00101-5.View ArticlePubMedGoogle Scholar
- Plaisier I, de Bruijn JG, Smit JH, de Graaf R, ten Have M, Beekman AT, van Dyck R, Penninx BW: Work and family roles and the association with depressive and anxiety disorders: differences between men and women. J Affect Disord. 2008, 105: 63-72. 10.1016/j.jad.2007.04.010.View ArticlePubMedGoogle Scholar
- Lubin B, Gardener SH, Roth A: Mood and somatic symptoms during pregnancy. Psychosom Med. 1975, 37: 136-146.View ArticlePubMedGoogle Scholar
- Kelly RH, Russo J, Katon W: Somatic complaints among pregnant women cared for in obstetrics: normal pregnancy or depressive and anxiety symptom amplification revisited?. Gen Hosp Psychiatry. 2001, 23: 107-113. 10.1016/S0163-8343(01)00129-3.View ArticlePubMedGoogle Scholar
- Brown S, Lumley J: Physical health problems after childbirth and maternal depression at six to seven months postpartum. BJOG: An International Journal of Obstetrics and Gynaecology. 2000, 107: 1194-1201. 10.1111/j.1471-0528.2000.tb11607.x.View ArticleGoogle Scholar
- Naerde A, Tambs K, Mathiesen KS, Dalgard OS, Samuelsen SO: Symptoms of anxiety and depression among mothers of pre-school children: effect of chronic strain related to children and child care-taking. J Affect Disord. 2000, 58: 181-199. 10.1016/S0165-0327(99)00119-6.View ArticlePubMedGoogle Scholar
- Swendsen JD, Merikangas KR: The comorbidity of depression and substance use disorders. Clin Psychol Rev. 2000, 20: 173-189. 10.1016/S0272-7358(99)00026-4.View ArticlePubMedGoogle Scholar
- Mattisson C, Bogren M, Horstmann V, Tambs K, Munk-Jorgensen P, Nettelbladt P: Risk factors for depressive disorders in the Lundby cohort--a 50 year prospective clinical follow-up. J Affect Disord. 2009, 113: 203-215. 10.1016/j.jad.2008.07.002.View ArticlePubMedGoogle Scholar
- Pajulo M, Savonlahti E, Sourander A, Herenius H, Piha J: Antenatal depression, substance dependency and social support. J Affect Disord. 2001, 65: 9-17. 10.1016/S0165-0327(00)00265-2.View ArticlePubMedGoogle Scholar
- Ulrich-Jakubowski D, Russell DW, O'Hara MW: Marital adjustment difficulties: Cause or consequence of depressive symptomatology?. J Soc Clin Psychol. 1988, 7: 312-318. 10.1521/jscp.1922.214.171.1242.View ArticleGoogle Scholar
- Wittchen HU, Pfister H: DIA-X Interviews (M-CIDI). 1997, Frankfurt, Germany: Swets & ZeitlingerGoogle Scholar
- Gjerde L, Røysamb E, Czajkowski N, Reichborn-Kjennerud T, Ørstavik RE, Kendler KS, Tambs K: Strong genetic correlation between interview-assessed internalizing disorders and a brief self-report symptom scale. Twin Res Hum Genet.
- Hartge P: Participation in population studies. Epidemiology. 2006, 17: 252-254. 10.1097/01.ede.0000209441.24307.92.View ArticlePubMedGoogle Scholar
- Chokka P: Postpartum Depression: Part 1. The Canadian Journal of CME. 2002, 14: 37-48.Google Scholar
- Hayes BA, Muller R, Bradley BS: Perinatal depression: a randomized controlled trial of an antenatal education intervention for primiparas. Birth. 2001, 28: 28-35. 10.1046/j.1523-536x.2001.00028.x.View ArticlePubMedGoogle Scholar
- The pre-publication history for this paper can be accessed here:http://www.biomedcentral.com/1471-2458/11/161/prepub
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