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To evaluate the effectiveness and cost effectiveness of an intensive home visiting programme in improving outcomes for vulnerable families.
Multicentre randomised controlled trial in which eligible women were allocated to receive home visiting (n=67) or standard services (n=64). Incremental cost analysis.
40 general practitioner practices across 2 counties in the UK.
131 vulnerable pregnant women.
Selected health visitors were trained in the Family Partnership Model to provide a weekly home visiting service from 6 months antenatally to 12 months postnatally.
Mother–child interaction, maternal psychological health attitudes and behaviour, infant functioning and development, and risk of neglect or abuse.
At 12 months, differences favouring the home‐visited group were observed on an independent assessment of maternal sensitivity (p<0.04) and infant cooperativeness (p<0.02). No differences were identified on any other measures. A non‐significant increase in the likelihood of intervention group infants being the subject of child protection proceedings, or being removed from the home, and one death in the control group were found. The mean incremental cost per infant of the home visiting intervention was £3246 (bootstrapped 95% CI for the difference £1645–4803).
This intervention may have the potential to improve parenting and increase the identification of infants at risk of abuse and neglect in vulnerable families. Further investigation is needed, along with long‐term follow‐up to assess possible sleeper effects.
Multiple studies undertaken over many years attest to the effect of parenting on the development of children and young people,1,2 and on their mental3,4,5 and physical health in adult life.6,7 Good quality, timely support for parents has now been identified in national and international policy documents as important for reducing social inequalities in health,8 preventing mental illness,9,10,11 and enhancing social and educational development.12
Questions remain, however, about how best to enable improvements in parenting in vulnerable families where parenting skills are poor, social and environmental risk factors are high, and a considerable risk of abuse or neglect exists. Children growing up in such families have a high incidence of emotional and behavioural problems, school failure, delinquency in childhood and adolescence, and psychological and social difficulties as adults.13
Home visiting programmes have been posited as one approach to supporting parenting in vulnerable families, and such programmes are now being used in countries such as the USA, Australia and New Zealand. Although the evidence base suggests that these programmes are not uniformly effective, recent reviews of reviews conclude that they can support parents, change parenting practices and improve infant outcomes.14 A small number of studies in the UK15,16,17,18 have compared the effectiveness of different types of home visiting programmes with standard health visiting, but none has dealt with the effectiveness of such programmes with parents who have been identified prenatally as being at high risk of poor parenting.
A multicentre randomised controlled trial (RCT) was conducted comparing home visiting with standard treatment. After consent and the collection of baseline data, randomisation was undertaken using sequentially numbered sealed opaque envelopes (fig 11).). Ethical approval was given by the Oxford Psychiatric Research Ethics Committee.
All parents randomised to the intervention group received 18 months of weekly visits from a health visitor trained in understanding the processes of helping, skills of relating to parents effectively and methods of promoting parent–infant interaction using the Family Partnership Model.19 Parents in both the control and intervention groups continued to receive the standard help currently available to such families.
Community midwives attached to 40 participating general practitioner practices across 2 counties screened women using a range of demographic and socioeconomic criteria (eg, mental health problems or housing problems). Women not wishing to be randomised or without a working understanding of English were excluded.
The study was powered to detect a change of 0.5 standard deviations (SDs) on one measure of mother–child interaction (the CARE Index) and one measure of maternal mental health (the General Health Questionnaire), allowing for a 25% loss to follow‐up and using 80% power.
Data were collected, coded and analysed by researchers who had not been involved in recruitment and were therefore blind to the intervention group.
Resource‐use data were obtained as an integral part of the trial data collection forms. Women were asked to maintain a diary of service use to aid recall. Unit costs (2003–4) were then attached to the items of resource use to identify a mean difference in costs between the two arms of the trial.20 Recommended discount rates of 3.5% were used for both costs and benefits where applicable.21 The perspective of the study was societal (ie, health service, social services, legal and housing costs were included).
An intent‐to‐treat analysis was conducted using univariate analysis of covariance for continuous variables and multivariate analysis of covariance for continuous variables in which the predictor variable comprised multiple scales. Significance was assessed at the 0.05 level. All analyses were adjusted for baseline scores and for baseline level of risk as indicated by the number of risk factors present at screening. Relative risk (RR) was calculated for dichotomous variables along with 95% confidence intervals (CIs).
Home visiting is a holistic intervention from which a wide range of positive outcomes have been reported14; therefore, several measures of outcome were included.
Mother–infant interaction was assessed at 12 months on the basis of a 3‐min video recording and coded for maternal sensitivity and infant cooperativeness using the CARE Index.22 One researcher, blinded to the intervention group, coded all videotapes and a random sample of 10% of videos was independently coded. A 2‐point difference was observed for 92% of codings for maternal sensitivity and for 75% of codings for infant cooperativeness.
Parenting attitudes and competence were assessed at 6 and 12 months using the Adult Adolescent Parenting Inventory.25 Parenting competence/confidence and experiences were measured at 12 months using the Parenting Sense of Competence scale26 and What Being the Parent of a Baby is Like (WBPB).27
Social support, marital/partner discord, self‐esteem, perceived self‐efficacy and parenting stress were assessed at 6 and 12 months using the Social Support Questionnaire,28 the Rust Inventory of Marital State,29 Rosenberg Self‐Esteem Inventory,30 Generalised Self‐Efficacy Scale31 and the Parenting Stress Inventory.32
The quality of the infant's home environment was assessed at 12 months using the HOME Inventory,33 and infant–toddler social and emotional adjustment was assessed using the Brief Infant–Toddler Social and Emotional Assessment,34 comprising two subscales: competence and problems. Infant development was assessed independently at 12 months using the Bayley Scales of Infant Development.35 Maternal assessment of the infant's temperament was measured using the Infant Temperament Scale (ITS).36 Parents were also asked to report infant well‐being at 6 months (eg, feeding, immunisation, disability). Participating health visitors provided data relating to case conferences, children on the protection register, children removed from the home and child deaths. Demographic details were collected from all respondents at baseline.
In all, 162 women were eligible and 20% (n=31) of these refused. No significant differences were found between the refusers and those who agreed to participate.
Dropout rate from the intervention was 3% and attrition <10%. Table 11 shows the distribution of demographic and other risk factors for the sample.
The mean number of risk factors per woman was five in both the intervention and control groups, but a slightly larger number of women in the intervention group were classified as high risk (22.4% of home‐visited women had 8 risk factors compared with 14.1% of the control group). We found no differences between the groups in any of the measures collected at birth, including gestational age, birth weight or method of delivery. Women in the control group had a mean of 9.2 visits by health visitors compared with 41.2 visits in the intervention arm. The intervention group received on average two thirds of the total possible number of visits (n=72).
We found no statistically significant differences between the two groups in scores on the Edinburgh Postnatal Depression Scale.
A larger but non‐significant proportion of infants in the home visiting arm were breast fed up to 6 months (55% v 45%), and minor disabilities were detected (9.7% v 1.7%). A smaller but again non‐significant proportion of home‐visited infants were admitted to hospital during the first 6 months after birth (8.5% v 14.5%). No differences were seen between the groups with respect to the introduction of solids before 12 weeks, the mean number of days stayed in hospital or uptake of immunisations.
No significant differences were observed between the two groups at 6 months in any of the standardised parent‐report outcomes (mental health self‐esteem, self‐efficacy, social support, relationship with partner) (table 22).
Results for the CARE Index suggest that women in the intervention arm were significantly more sensitive to their babies (p=0.04), who were significantly more cooperative (p=0.02) (table 33).
No significant differences were found between the two arms on the remaining two independent measures: the HOME Inventory or Bayley Scales.
Similar numbers of child protection issues were identified in the two groups between 6 and 12 months of age (17% home visiting groups and 15% control group), but a non‐significant increase in the likelihood of placement on the child protection register or care proceedings in the intervention group (RR 2.02, 95% CI 0.46 to 2.54) and a non‐significant difference in the proportion of children being removed from the home (6% v 0%) were observed. Half of these children were returned to the home at a later date. One child died in the control group, for whom child protection concerns were raised.
One significant group effect was identified for social support (p>0.004), indicating a greater fall‐off in social support in the control group, possibly due to the low response to this question at follow‐up. No significant group, time, or time by group effects were observed for any other parent‐report measures (table 44).
The mean costs per infant in the intervention and control arms were £7120 v £3874, a statistically significant difference of £3246 (bootstrapped 95% CI for the difference £1645–4803). The total costs of the intervention arm were greater because of increased home visits, phone calls to home visitors, appointments with psychologists, psychiatrists, foster care, adoption and home visitor training costs. However, there were cost savings for clinic health visiting, hospital accident and emergency visits for infants and mothers, and alcohol and drug counselling. The incremental cost per child “identified” as being ill‐treated on the basis of child protection proceedings between 6 and 12 months was £54370.
The results of this study suggest that early home visiting based on the Family Partnership Model can improve the sensitivity and attunement of high‐risk mothers to their infants and infant cooperativeness. However, because there were no significant differences between the two groups for most of the large number of outcomes measured, it is possible that this one positive finding occurred by chance. Most of the findings favoured the intervention group, but lacked statistical significance, suggesting that the study may also have been underpowered.
Focus group discussions with the health visitors delivering the intervention37 and in‐depth one‐to‐one interviews with participating mothers38 provide a contrasting insight into the effect of the programme from that offered by the quantitative data.38,39 Although these qualitative data cannot provide evidence of overall effectiveness, they suggest that the participants experienced changes, that would not have been captured with the standardised outcome instruments used in this trial.
This home visiting programme seemed to have increased the number of cases of abuse identified in the intervention arm. This outcome is often treated as an example of surveillance bias. An alternative view recognises such an outcome as a valuable secondary prevention of the deleterious consequences of abuse. Improvements in health visitors' sensitivity to abusive parenting may have enabled them to institute child protection proceedings at an earlier stage in the child's life, reducing the length of exposure to damaging environments by placing infants with substitute parents during the first year of life. Such a view is supported by new research, which suggests that abused children adopted in infancy fare much better than children adopted after 4 years of age.39 The one death in the control group about which there were child protection concerns did not achieve statistical significance because of the small sample size, but may nevertheless have been an important finding.
This study provides evidence to suggest that this intensive home visiting programme may improve parenting in vulnerable families and increase identification of abuse and neglect in infancy for an added cost of £3246 per child. Further follow‐up is needed to identify potential sleeper effects and to assess the longer‐term effect on child abuse. Meanwhile, uncertainty surrounding the results means that the case for provision is not strong, and suggests the need for further research both to confirm the findings and possibly to increase the efficacy of the programme.
RCT - randomised controlled trial
Funding: Department of Health, Nuffield Foundation.
Competing interests: None.