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To determine whether a community‐delivered intervention targeting infant sleep problems improves infant sleep and maternal well‐being and to report the costs of this approach to the healthcare system.
Cluster randomised trial.
49 Maternal and Child Health (MCH) centres (clusters) in Melbourne, Australia.
328 mothers reporting an infant sleep problem at 7 months recruited during October–November 2003.
Behavioural strategies delivered over individual structured MCH consultations versus usual care.
Maternal report of infant sleep problem, depression symptoms (Edinburgh Postnatal Depression Scale (EPDS)), and SF‐12 mental and physical health scores when infants were 10 and 12 months old. Costs included MCH sleep consultations, other healthcare services and intervention costs.
Prevalence of infant sleep problems was lower in the intervention than control group at 10 months (56% vs 68%; adjusted OR 0.58 (95% CI: 0.36 to 0.94)) and 12 months (39% vs 55%; adjusted OR 0.50 (0.31 to 0.80)). EPDS scores indicated less depression at 10 months (adjusted mean difference −1.4 (−2.3 to −0.4) and 12 months (−1.7 (−2.6 to −0.7)). SF‐12 mental health scores indicated better health at 10 months (adjusted mean difference 3.7 (1.5 to 5.8)) and 12 months (3.9 (1.8 to 6.1)). Total mean costs including intervention design, delivery and use of non‐MCH nurse services were £96.93 and £116.79 per intervention and control family, respectively.
Implementing this sleep intervention may lead to health gains for infants and mothers and resource savings for the healthcare system.
Current Controlled Trial Registry, number ISRCTN48752250 (registered November 2004).
Maternal depression impacts adversely on maternal quality of life, mother–child relationships and child development.1,2 Despite a prevalence of 15% in the first year postpartum,3 depression often remains undiagnosed and, even if detected, many mothers reject the diagnosis, the treatment or both.4
Maternal depression is linked to poor infant sleep. Problems with frequent night waking and difficulties settling to sleep are reported by over a third of parents in the second 6 months of life5,6 and are consistently associated with poor maternal health.7,8,9
In a previous efficacy trial, we demonstrated that treating infant sleep problems (simple behavioural techniques delivered in local well‐child centres over two to three sessions) significantly reduced maternal reports of depression symptoms as well as infant sleep problems.10 However, efficacy and generalisability may be limited by the predominantly middle‐class status of participating families and the fact that the intervention was delivered by a single paediatrician (HH). In another randomised trial,11 a single, nurse‐led consultation emphasising ways to help very young infants settle to sleep independently resulted in intervention infants sleeping more than controls at age 12 weeks but in no change in maternal depression. All other sleep intervention trials have been limited by selection bias, small sample sizes, short follow‐up and/or lack of randomisation.12
The trial reported here was conducted within an existing universally available, state‐wide primary health care service, training the well‐child care providers themselves to manage infant sleep problems in families from a broad sociodemographic sample. We hypothesised that a brief behavioural intervention designed to reduce infant sleep problems would result in improved infant sleep and maternal well‐being. We also documented the costs of the intervention and costs to the healthcare system.
The trial was conducted in greater Melbourne (population 3.4 million), Victoria, Australia. Melbourne has 31 local government areas (LGAs), each with around 750 births per annum. LGAs were ranked by the census‐derived Socio‐Economic Indexes For Areas (SEIFA) Index of Relative Disadvantage (Australian Bureau of Statistics, 2001), and thence divided into tertiles representing low, middle and high socioeconomic status. From each tertile, two LGAs were selected; all Maternal and Child Health (MCH) nurses in these six LGAs participated.
Every infant born in the state of Victoria is assigned a MCH nurse, and 91% of parents attend the free health visit offered at 4 months of age.13 MCH nurses consecutively invited mothers of 4‐month‐old infants attending in October–November 2003 to take part in the Infant Sleep Study. Infants born before 32 weeks' gestation and mothers with insufficient English to complete questionnaires were excluded. The research team telephoned interested mothers and mailed the baseline questionnaire to be returned with written informed consent.
When infants turned 7 months, MCH centres (and therefore their mothers) were randomly allocated (stratifying by LGA) to intervention or control arms by an independent statistician (fig 1). Centres were ranked within each stratum according to the number of infants recruited at 4 months, randomising the largest centre and alternately allocating subsequent ones to avoid a marked imbalance in cluster sizes between trial arms. As all the centres were recruited prior to randomisation and ranked using a criterion that could not be influenced by the investigators, allocation concealment was achieved. Mothers reporting an infant sleep problem in the concurrent 7‐month questionnaire comprised the study sample.
Intervention nurses attended two 2.5 h training sessions conducted by HH (paediatrician) and JB (child psychologist). Training incorporated didactic teaching, written information, role play and trouble shooting common problems (eg, partner conflict over sleep management).
Intervention mothers were advised by letter that their MCH nurse was trained to provide advice to help manage their infant's sleep. At the first consultation (8‐month well‐child visit) nurses elicited the nature of the sleep problem, identified solutions, and wrote an individualised sleep management plan with the mother. Two handouts discussed normal sleep patterns at 6–12 months and sleep associations and their causal role in sleep problems. Handouts on managing problem overnight feeding (ie, reducing volume/time spent feeding over a week) and dummies (ie, removal or teaching infant to replace own dummy) were also available.
Mothers were offered the choice of two behavioural interventions: i) “controlled crying” whereby parents respond to their infant's cry at increasing time intervals, to allow independent settling14,15 or ii) “camping out”, ie, sitting with their infant until they fell asleep and gradually removing parental presence over 3 weeks. Mothers maintained daily sleep diaries until the follow‐up appointment 2 weeks later, to facilitate recognition of sleep patterns and improvements and to help set further goals.
Mothers completed written questionnaires at 4 months (sociodemographic details), 7 months (prior to randomisation, to establish the presence of a sleep problem), and at 10 and 12 months (to measure outcomes). The primary outcome was maternal report of infant sleep (“Over the last 2 weeks, has your baby's sleep generally been a problem for you?” Yes/No), an established indicator of frequent and prolonged night wakings.6 Maternal well‐being was a secondary outcome, measured by the 10‐item Edinburgh Postnatal Depression Scale (EPDS)16 (community cut‐point for depression is a score >917) and the SF‐12,18 a 12‐item, validated, measure of physical and mental health with higher scores indicating better health. Other validated outcome measures were maternal sleep quality and quantity (using a 4‐point ordinal question,19 and dichotomised at the midpoint into good versus bad quality and enough versus not enough quantity), and maternal rating of infant temperament (5‐point Global Infant Temperament Scale20 higher scores indicate a more difficult baby). Mothers also rated their confidence in their nurse's health advice, on a 4‐point, ordinal, study‐designed scale. Intervention mothers' reported satisfaction with and usefulness of the sleep information in treating their infant's sleep problem, on 10‐cm visual analogue scales.6 They reported how often they used the strategies (from “none of the time” to “all of the time”) and degree of support they received from their partner when using the sleep strategies (4‐point scale ranging from “hardly ever supported me” to “supported me almost all the time”). All mothers were asked if they had received help other than that given in the study and, if so, from where (eg, stay at a parenting centre). In the 12‐month questionnaire, intervention mothers also rated specific advice/strategies given by their nurse as “helpful” or “unhelpful”.
At 10 and 12 months, mothers reported on the number of MCH visits for sleep advice and non‐MCH nurse professional health care (eg, parenting centres, family doctor) and non‐professional care (eg, books, relatives). Nurses provided information on number and duration of sleep visits for mothers in the intervention group. The cost of intervention materials (design and production) and nurse training programme (design and delivery) was calculated from research budgets, with total cost allocated equally over all intervention group mothers.
Nurse visits, outreach visits and telephone support costs were calculated using average MCH nurse salary data. Admissions to a parenting centre were valued using cost estimates from two of eight Melbourne centres. Other health service use costs were calculated using Medicare Benefits Schedule fees.21
Project approval was obtained from the Ethics in Human Research Committee of Melbourne's Royal Children's Hospital (23067B). The trial was conducted in accordance with the CONSORT statement for cluster randomised trials.22
To detect a difference of 20% (70% in the control group and 50% in the intervention group) in the primary outcome, an individually randomised trial would require 103 infants in each arm to have 80% power at the 5% level of significance. This sample size was inflated by a design effect of 1.2 to 124 infants per trial arm to allow for correlation between responses within the same cluster (ie, MCH centre),23 with an expected average cluster size of 11 (ie, number of eligible mothers attending the centre) and intraclass correlation coefficient (ICC) of 0.02.
Analyses were conducted on an “intention to treat” basis. Outcomes and costs were compared between the intervention and control groups at 10 and 12 months, adjusted for potential confounders identified in our previous research6,10 and determined a priori (see tables 11 and 2). Tests of interaction assessed whether the impact of the intervention on the sleep problem and the quantitative EPDS outcome was greater amongst mothers with high baseline depression scores (EPDS>9) than mothers with low scores.
To allow for clustering, quantitative outcomes and costs were analysed using random effects linear regression24 and dichotomous outcomes were analysed using logistic regression by fitting marginal models using generalised estimating equations (GEE) with “robust” estimates of standard error25 and a specified exchangeable correlation matrix. For GEE analyses where the ICC was negative, the results from standard logistic regression are reported. All quantitative outcomes and costs (except the Global Infant Temperament score) were skewed and, therefore, results were validated by non‐parametric bootstrapping.26 Bootstrap confidence intervals were similar to the confidence intervals from the main analyses, so the latter are reported. Analyses were conducted using Stata 8 (Stata, College Station, TX).
Response rates were 739 of 1025 eligible mothers at 4 months (72%) and 695 (68%) at 7 months, of whom 328 reported a problem with their infant's sleep and were therefore participants in the trial. Intervention (n=174) and control mothers (n=154) had similar infant, sleep, maternal and sociodemographic characteristics (table 33).). Most mothers (84%) reported insufficient sleep which was of poor quality (55%).
At 10 months, 56% of intervention and 68% of control mothers reported infant sleep problems (OR 0.61, p=0.04); at 12 months, this fell to 39% vs 55% (OR 0.53, p=0.007). Thus to resolve one infant sleep problem, 8.3 infants would be need to be treated at 10 months and 6.3 infants at 12 months. After adjusting for potential confounders (table 11),), the odds of reporting a sleep problem in the intervention group were 42% lower at 10 months and 50% lower at 12 months compared with controls.
At 10 months (table 11),), 28% of intervention mothers and 35% of control mothers scored >9 on the EPDS, indicating clinically significant depression (adjusted OR 0.63, p=0.11); comparable figures at 12 months were 25% vs 28% (adjusted OR 0.71, p=0.26). Intervention mothers had lower mean EPDS scores than controls at both 10 months (6.8 vs 7.8, adjusted mean difference −1.4, p=0.007) and 12 months (5.9 vs 7.2, adjusted mean difference −1.7, p=0.001) and higher mental health (SF‐12) scores at both 10 months (48.1 vs 45.0, p=0.001) and 12 months (49.7 vs 46.1, p<0.001). Physical health was similar at 10 months but unexpectedly poorer in intervention mothers at 12 months (mean score 50.8 vs 52.7, adjusted mean difference −1.7, p=0.04).
Fewer intervention than control mothers reported poor sleep quality at 10 months (63% vs 72%, adjusted p=0.16) and 12 months (52% vs 63%, adjusted p=0.01), and insufficient sleep at 10 months (40% vs 46%, adjusted p=0.27) and 12 months (34% vs 45%, adjusted p=0.02).
In subgroup analyses (table 22),), the effect of the intervention on depression symptoms at 10 months was greater for mothers whose initial EPDS score was >9.
Table 44 shows the strategies intervention mothers found helpful. Mothers were generally satisfied with the intervention strategies (median 7.7, interquartile range (IQR) 5.5–9.2) and found them useful (median 7.3, IQR 3.0–9.1). The majority (56%) used the sleep strategies “most” to “almost all of the time”; only 7% reported no use. Most mothers (80%) reported partner support with sleep strategies.
Mean costs for the intervention versus control group were £96.93 (SD 249.37) versus £116.79 (SD 330.31), respectively (mean difference −£19.44 (95% CI −83.70 to 44.81), p=0.55). In the intervention group 100 mothers attended their nurse to discuss infant sleep for an average of 1.52 visits, while in the control group 30 mothers attended for an average of 1.32 visits. Across all mothers, this gives an average reported use of nurse sleep‐related visits of 0.9 and 0.3 for intervention versus control mothers, respectively. The mean duration of the first sleep visit was 25 min and 19 min for subsequent visits.
Control mothers were more likely than intervention mothers to have sought help from professional services for infant's sleep (33% vs 18%, p=0.02; see table 55).
A brief behavioural intervention delivered by primary healthcare professionals reduced infant sleep problems, improved maternal mental health, and reduced the amount of paid professional help sought for infant sleep problems 2 and 4 months after intervention. Benefits occurred across a broad sociodemographic range and at lower cost to the healthcare system.
This is the first trial examining the impact of a primary care infant sleep intervention on infant sleep and maternal well‐being. Over 95% of mothers and all clusters remained in the trial. Although only 72% of eligible mothers entered the study at 4 months, their mean EPDS score (mean 6.8, standard deviation (SD) 4.9) was similar to that reported in sample of women in Victoria 8–9 months postpartum (mean 7.6, SD 4.8).27 The prevalence of reported sleep problems (47%) was similar to that in our earlier study6 but higher than the 36% reported by mothers in another community study of Australian infants aged 7–9 months.5 This might suggest that mothers experiencing early sleep problems were more likely to enter the study but should not limit generalisability to English‐speaking mothers with infant sleep problems in the general population.
There is no accepted definition of an infant sleep problem. However, mothers who report an infant sleep problem are known to have babies with longer and more frequent night wakings and greater settling difficulties, and to suffer poorer mental health.6 Parents reporting a child sleep problem are also more accurate reporters of their child's sleep patterns than parents not reporting a child sleep problem when compared with over‐night infra‐red camera footage.28
Neither nurses nor mothers could be blind to group membership during the intervention and mothers' self‐reported outcomes. This may have biased reports of the intervention mothers towards an apparent benefit. However, intervention mothers reported a worse physical health outcome which argues against such a bias.
The trial demonstrated a sustained reduction in infant sleep problems, similar in size to that reported in other trials of behavioural interventions with shorter follow‐up periods.12 At 12 months, mean SF‐12 mental health scores for intervention and control mothers were 50 and 46, respectively. In a large, representative Australian population survey, adults scoring 40–49 vs 50 on the SF‐12 were almost four times as likely to have a current mental disorder, and more than twice as likely to have impaired daily functioning.29 Thus this trial's SF‐12 mental health scores suggest an important impact on mental health disability. Similarly, the improvement in maternal sleep quality and quantity at 12 months might reduce other problems associated with maternal sleep deprivation, that is, maternal overload and dysfunction30 and later child behaviour problems.31
The chosen perspective of the economic evaluation meant we excluded resource use and costs that fell solely on mothers, for example out‐of‐pocket costs in accessing services. If the intervention reduces use of professional health services (apart from MCH nurses), it may well also reduce personal costs to mothers as mothers usually live within walking distance of their nurse's centre. Although the costs for mothers in the intervention arm were reduced relative to the control arm, the confidence intervals for the difference suggest that the cost could be greater in the intervention arm, in which case one would need to consider incremental costs. Equally, intervention costs could be even lower, as we included costs of material development which would not be re‐incurred if the programme were taken up more widely.
In conclusion, this brief intervention was effective, feasible, and acceptable to parents and primary healthcare providers alike. Effects were consistent across measures and over time, and occurred at a lower cost to the healthcare system. The challenge now is to translate this intervention to the wider population in a sustainable and feasible way.
We would like to thank the MCH nurses and families of the cities of Bayside, Darebin, Hobson's Bay, Manningham, Monash and the shire of Yarra Ranges who took part in this study.
The trial design was formulated by HH and MW. JB, HH and AH implemented the trial. Data management and analysis was implemented by OU, LG and AH with HH, MW and JB contributing to the analysis plan. HH produced the first draft of the paper with all other authors contributing to subsequent drafts. HH will act as guarantor for the paper.
EPDS - Edinburgh Postnatal Depression Scale
GEE - generalised estimating equations
ICC - intraclass correlation coefficient
IQR - interquartile range
LGA - local government area
MCH - Maternal and Child Health
SEIFA - Socio‐Economic Indexes For Areas
Funding: This project was funded by the National Health and Medical Research Council Project, grant number 237120 and The Pratt Foundation. Dr Hiscock was supported by the Murdoch Childrens Research Institute. None of the funders played a role in the study design, collection analysis or interpretation of the data or in the decision to submit.
Competing interests: None.