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Abstract
Objective To examine the efficacy of psychological and psychosocial interventions for reductions in repeated self-harm.
Design We conducted a systematic review, meta-analysis and meta-regression to examine the efficacy of psychological and psychosocial interventions to reduce repeat self-harm in adults. We included a sensitivity analysis of studies with a low risk of bias for the meta-analysis. For the meta-regression, we examined whether the type, intensity (primary analyses) and other components of intervention or methodology (secondary analyses) modified the overall intervention effect.
Data sources A comprehensive search of MEDLINE, PsycInfo and EMBASE (from 1999 to June 2016) was performed.
Eligibility criteria for selecting studies Randomised controlled trials of psychological and psychosocial interventions for adult self-harm patients.
Results Forty-five trials were included with data available from 36 (7354 participants) for the primary analysis. Meta-analysis showed a significant benefit of all psychological and psychosocial interventions combined (risk ratio 0.84; 95% CI 0.74 to 0.96; number needed to treat=33); however, sensitivity analyses showed that this benefit was non-significant when restricted to a limited number of high-quality studies. Meta-regression showed that the type of intervention did not modify the treatment effects.
Conclusions Consideration of a psychological or psychosocial intervention over and above treatment as usual is worthwhile; with the public health benefits of ensuring that this practice is widely adopted potentially worth the investment. However, the specific type and nature of the intervention that should be delivered is not yet clear. Cognitive–behavioural therapy or interventions with an interpersonal focus and targeted on the precipitants to self-harm may be the best candidates on the current evidence. Further research is required.
- MENTAL HEALTH
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Strengths and limitations of this study
We used robust systematic review methodology, including analysis of meaningful secondary outcomes, and sensitivity analysis to assess the impact of risk of bias on the results.
Our search was thorough and has identified 45 relevant randomised controlled trials; this is the largest number of trials identified in a systematic review of this type.
The risk of bias in various domains was rated as high, and sensitivity analyses when restricted to a limited number of high-quality studies showed that this benefit was non-significant.
There were few trials of some types of interventions undertaken, limiting the power of the analysis to show an effect in meta-regression.
Results of the meta-regression are observational in nature and cannot infer causality; as such, they are considered to be hypothesis generating rather than providing robust conclusions.
Introduction
Clinically treated non-fatal self-harm (we use the term self-harm henceforth) is common. A landmark systematic review of 90 observational studies from Western countries estimated a 1-year repetition rate of self-harm of 16%, while the suicide rate was 2% after 1 year and 7% after 9 years.1 A more recent review of 177 studies from Western and non-Western countries indicated little change in these estimates, with reported repetition of self-harm of 16.3% after 1 year, while the suicide mortality rate was 1.6% after 1 year and 3.9% after 5 years.2 Self-harm is problematic in terms of adverse outcomes such as repetition of self-harm, suicide and all-cause mortality; mental health morbidity, quality of life and physical, psychological and social functioning. It is also costly in terms of immediate and ongoing treatment.1 ,2
Despite this, there is relatively limited evidence about the efficacy of psychological and psychosocial interventions to prevent the repetition of self-harm,3–6 particularly because of the limited number of trials, the small sample size of many trials and the diversity of interventions tested. Large-scale randomised controlled trials (RCTs) are considered to be difficult to conduct due to ethical concerns regarding withholding potentially efficacious interventions (in the control group) from people at risk.7 ,8 In addition, studies are frequently underpowered,8–10 lack a standardised definition of self-harm11 ,12 and have marked differences in assessment tools and reporting of outcomes, which leads to difficulties in pooling data.
A seminal Cochrane review of 23 RCTs published in 199913 examining the efficacy of psychological and pharmacological interventions for reducing repeat self-harm in any clinical population included an analysis of risk of bias; and (where possible) meta-analyses of therapies and medications classified by type of therapy and type of medication. The authors concluded that there was potential benefit of problem-solving therapy (five studies), the provision of an emergency access card (two studies) and, based on one study each, of depot flupenthixol treatment and dialectical behavioural therapy (DBT) in reducing repetition of self-harm. Overall the conclusions were that there remained considerable uncertainty with regard to the efficacy of any intervention for repeat self harm. The recently published Cochrane reviews that update this evidence show (1) that few pharmacological interventions have any statistically significant effect on reducing repetition of self-harm, except flupenthixol, for which there is one low-quality trial to date14 and (2) that there is some evidence that cognitive–behavioural therapy (CBT) (and not problem-solving therapy) can reduce repetition of self-harm in unselected populations, but again highlight the poor quality of the evidence base.15
In addition to these Cochrane reviews, a number of trials have been published and several systematic reviews produced that aim to highlight what interventions are most efficacious.16–25 Reviews have been based on narrative summaries of indirect comparisons (using data from separate trials, in contrast to direct comparison in head-to-head RCTs) and endorsed CBT,3 ,20 ,23 ,26 DBT19 ,23 ,26 and problem-solving therapy;5 ,26 one has endorsed psychodynamic therapy.23 However, they have been unable to provide definitive guidance about whether the type of intervention delivered, individual components of interventions or components of study methodology modify the overall treatment. This is because they have either only examined the effects of specific types of interventions, or the efficacy of interventions in specific clinical populations/diagnostic groups, or have been limited by non-systematic search strategies, absent quality appraisal techniques, a lack of quantitative synthesis and techniques to appropriately investigate such modifying effects.
The National Institute for Health and Care Excellence (NICE) recommends “Consider offering 3 to 12 sessions of a psychological intervention that is specifically structured for people who self-harm, with the aim of reducing self-harm” (ref. 27, p. 10). The guidelines include cautious recommendations about the type of therapy to offer, ‘the intervention should be tailored to individual need, and could include cognitive–behavioural, psychodynamic or problem-solving elements’. This cautious approach is appropriate given that, to date, the evidence for which types of psychotherapy are more effective has been derived from narrative summaries of indirect comparisons.
A more sophisticated quantitative analysis is therefore needed to robustly explore this question. One method for doing this is meta-regression.28 This approach has been useful in other populations by examining the capacity for the type of psychological interventions to modify outcomes. For example, a meta-regression of trials of Collaborative Care interventions for depression in primary care found that the particular type of Collaborative Care provided modified the intervention effect.29 A meta-regression of psychological interventions in primary care also showed that the type of psychological intervention did not modify the overall effects of intervention on depression and anxiety symptoms compared with treatment as usual (TAU).30
It is currently unclear whether psychological interventions are beneficial overall and there is little evidence-based guidance to clinicians as to the specific type of psychological or psychosocial intervention to offer individuals in order to prevent repetition of self-harm. We planned to identify all relevant studies in order to calculate pooled estimates of efficacy overall and for interventions categorised by type, and to examine possible modifiers of treatment effect.
Methods
Aims
The aims of this systematic review are to (1) update the evidence base by evaluating the efficacy of psychological and psychosocial interventions to reduce repeat self-harm, (primary outcome) and to reduce suicidal ideation, depression and hopelessness (secondary outcomes) using meta-analysis; and (2) examine whether the type, intensity or other specific components of the interventions, or study methodology, modify the pooled intervention effect using meta-regression.
The conduct of the review is based on Cochrane systematic review methodology28 and conforms to the PRISMA checklist31 with regard to the reporting of the review (see online supplementary table S1). There is no registered protocol for this review.
Eligibility criteria for selecting studies
Only RCTs were eligible for inclusion as these are considered to provide the strongest measure of whether an intervention has an effect because this design minimises bias.32 These RCTs were of psychological or psychosocial interventions for adults (>18) who had recently presented to clinical settings, including but not limited to emergency departments and hospitals, having engaged in self-harm, which for the purposes of this review included behaviours variously referred to by trial authors as self-harm, deliberate self-harm, self-poisoning, deliberate self-poisoning, parasuicide or suicide attempt. We would have also accepted any studies using other alternate terms, for example, overdose or suicidal gesture. We excluded RCTs where it was clear that participants were recruited on the basis of having deliberately tried to injure themselves without suicidal intent (often referred to as non-suicidal self-injury, which is generally considered to be a different, although overlapping phenomenon).33 We did not impose any language restriction, for example, English language.
Interventions had to be primarily delivered directly to patients, as opposed to being aimed at the clinicians treating them. Trials of brief contact interventions, such as telephone contacts; crisis cards, or postcards; pharmacological interventions; and trials undertaken in subpopulations selected on the basis of borderline personality disorder (BPD), depressive disorder or psychosis were excluded with the aim of ensuring a homogeneous group of trials, given that one of our primary aims was to explore the modifying effects of the type and nature of psychological and psychosocial interventions delivered.
We included any comparator including TAU; enhanced TAU (TAU+), defined as seeking to ensure engagement in TAU; alternative controlled intervention; no treatment; and waitlist control.
The primary binary outcome was any repeat episode of self-harm (which included behaviours referred to by trial authors as deliberate self-harm, self-harm, self-poisoning, deliberate self-poisoning, parasuicide and suicide attempt). We did not set any limit on time to repetition and when data for more than one follow-up was provided, we selected the longest follow-up point. Secondary continuous outcomes included self-rated severity of suicidal ideation, depression and hopelessness measured on standardised scales. These secondary outcomes have been shown to be associated with self-harm34–36 and were considered to be important secondary outcomes in their own right.
Search strategy and key words
We first searched the reference list of the seminal Cochrane review on treatments for self-harm originally published in 19995 and recently updated.15 To find articles published since the original publication of this review, we undertook electronic searches of MEDLINE, PsycInfo and EMBASE (from 1999 to June 2016) using a combination of terms relevant to self-harm and terms designed to retrieve controlled trials (see online supplementary table S2 for MEDLINE search strategy). We also examined the reference lists of included trials and relevant reviews, and contacted experts in the field.
Study selection, data extraction and risk of bias assessment
Two authors (SEH and JR) independently selected trials and extracted data on characteristics of the trial (see online supplementary table S3) and on the nature of the psychological and psychosocial interventions (see online supplementary table S4), and outcome data using previously piloted data extraction forms. Discrepancies were resolved by a third author (GC).
supplementary table S3
General characteristics of included trials
Risk of bias was assessed independently by two authors (SEH and JR) based on Cochrane Collaboration methodology.37 Trials were assessed as being of low risk, unclear risk or high risk of bias in four domains: (1) random sequence generation; (2) allocation concealment; (3) blinding of outcome assessors; (4) extent, and management, of incomplete outcome data, in particular whether an intent-to-treat (ITT) analysis was conducted (see table 1).
Risk of bias
For the final domain (5), trials were judged as being of a low risk of bias if they had <15% missing data, as unclear risk if they had >15% missing data and conducted ITT analysis, and as high risk of bias if there was over 15% missing data and no ITT analysis or if it was not clear whether ITT analysis was conducted.
Statistical analyses
For all analyses, we used the Comprehensive Meta-Analysis (CMA) software (Comprehensive Meta-analysis [program]. 3 version. Englewood, NJ: Biostat, 2014).
Meta-analysis
For the primary outcome (any repetition of self-harm), we pooled data to calculate a risk ratio (RR) and, when this estimate was significantly different from 1, the number needed to treat (NNT). The secondary outcomes were all continuous outcomes. We converted suicidal ideation and depression scores to the standardised mean difference (SMD). Since hopelessness was uniformly measured using the Beck Hopelessness Scale, we used the mean difference. We pooled estimates of treatment effect using a random-effects model with 95% CIs.
Additional analyses
Meta-analysis sensitivity analyses
We undertook a sensitivity analysis to assess the impact of trials judged to be either at a high or unclear risk of bias, for the domains of allocation concealment and outcome assessor blinding, given that these have been shown to have the largest impact on effect estimates.83
Meta-regression
Owing to the restricted number of trials, we entered only one covariate in a series of random-effects regression models using the log RR and its corresponding 95% CIs to examine the type, intensity and components of the interventions and the study methodology, which we expected to have the strongest influence on repeated self-harm using a priori chosen independent variables:
Type of intervention, classified into six categories: problem-focused (including problem-solving therapy) interventions, CBT, complex intervention (that included various combinations of psychotherapy or case management with periods of inpatient care, assertive approaches to ensuring engagement such as flexibility with regard to where patients were seen, phone calls and reminders; and crisis management), and psychodynamic interpersonal, other-psychological and other-psychosocial therapy.
Intensity, scored as the total planned hours of therapy and/or contact.
Components of intervention: home visits; between-session contact emphasising motivation to attend; continuity of care between the acute hospital and outpatient setting; clinician access for crisis management; and the presence of an inpatient component.
Type of comparator condition: TAU, TAU+, alternative controlled intervention, no intervention or waitlist.
Study population defined by nature of the suicidal behaviour: self-harm (including where original studies used any synonyms or alternate definitions for self-harm, eg, deliberate self-harm or parasuicide), self-poisoning (including where original studies used the synonym deliberate self-poisoning) or suicide attempt.
Total sample size analysed.
Heterogeneity
Heterogeneity was assessed as per Cochrane methodology28 (I2 values of 0–40%: might not be important; 30–60%: moderate heterogeneity; 50–90%: substantial heterogeneity; 75–100%: considerable heterogeneity), taking into account (1) magnitude and direction of effects and (2) strength of evidence for heterogeneity (eg, p value from the χ2 test, or a CI for I2).
Assessment of reporting bias
Reporting bias (systematic differences between reported and unreported findings) was assessed by entering data into a funnel plot.
Results
Study selection
Ancestry searching of the existing Cochrane review5 identified 15 relevant trials. After removing duplicates, 4348 articles were retrieved from the search of electronic databases. Inspection of titles and abstracts resulted in the exclusion of 4218 articles. There were eight reviews for ancestry searching, including the newly published Cochrane review,6 ,14 ,23 ,24 ,26 ,84–86 from which seven relevant trials were identified. After full-text inspection of 137 articles, 92 were excluded. We included 30 new trials in addition to the 15 trials from the original Cochrane review. Of 45 included trials, 36 published usable data (based on 7354 participants) for meta-analysis of the primary outcome (see figure 1) and 37 provided data for at least one of the secondary outcomes.
Flow chart of study selection. BPD, borderline personality disorder; NSSI, non-suicidal self-injury; RCT, randomised controlled trial.
Study characteristics
A description of trial characteristics is shown in online supplementary table S3. The majority of trials that provided data for the primary outcome (n=19)41 ,42 ,48 ,52 ,55 ,56 ,60–62 ,65 ,67 ,69–72 ,74 ,75 ,77 ,78 ,87 were medium (80–280 participants), eight were small (<80 participants)38 ,44 ,47 ,49 ,50 ,58 ,81 ,82 and nine were large (>280 participants).39 ,40 ,43 ,54 ,57 ,59 ,63 ,68 ,79 Of the remaining trials that did not contribute data to the primary outcome, five trials were small,45 ,46 ,64 ,73 ,80 three were medium;51 ,53 ,76 and one was large.66
Types of participants
Twenty-one trials included participants on the basis of a recent episode of self-harm (variously referred to in the original studies as deliberate self-harm, self-harm, self-poisoning, deliberate self-poisoning or parasuicide by the trial authors; see online supplementary table S3)40 ,42 ,43 ,49 ,53–55 ,57 ,59–61 ,73 ,76–78 ,82 and 21 trials on the basis of what was specifically referred to as recent hospital-treated suicide attempt.45–48 ,50 ,51 ,56 ,58 ,63–65 ,67–72 ,74 ,75 ,79–81 One trial included participants on the basis of suicidal ideation with intent to die and/or suicide attempt;52 one trial included participants who had a recent episode of hospital or clinic-treated self-harm or suicide attempt.62 Inclusion criteria were unclear in one trial, but it is unlikely they were all hospital-treated66 (see online supplementary table S3).
Types of interventions
Forty-two trials were a simple comparison between an intervention and control arm. Seven tested CBT, and 15 tested complex interventions. The complex interventions with outreach included combinations of therapy or case management, plus various additional components (see online supplementary tablesupplementary table S4).
Three trials had three arms that included two active intervention arms and one control group. One compared cognitive restructuring, problem-solving and a non-directive supportive condition.45 The second compared a complex intervention, CBT and a no-intervention control.69 However, few participants randomised to CBT (5/82) received CBT, so we have only included two trial arms: the complex intervention arm and the no-intervention arm and omitted the CBT arm from analyses.69 The third compared CBT, problem-solving therapy and TAU.46
Control conditions
Thirty trials used TAU, and six used TAU+ as the comparator.38 ,43 ,48 ,54 ,58 ,63 Seven trials used an alternative controlled intervention,44 ,45 ,50 ,61 ,74–76 one trial64 used a waitlist control comparison condition and one trial69 used a no-intervention control comparison group (see online supplementary table S3).
Outcomes and measurement
In 13 trials, self-harm outcomes were measured by participant interview,42 ,43 ,48 ,50–53 ,58 ,63 ,69 ,71 ,73 ,74 in nine trials via medical records,39 ,46 ,47 ,57 ,59 ,60 ,62 ,65 ,67 in 13 by both,40 ,41 ,44 ,49 ,54–56 ,61 ,68 ,70 ,77 ,79 ,82 in one by self-report questionnaire,76 in two by self-report questionnaire and medical records;72 ,78 and in one via the national surveillance system;81 it was unclear in four;38 ,65 ,68 ,75 and these outcomes were not collected in two trials45 ,80 (see online supplementary table S3).
Risk of bias within studies
In 23 of the 45 trials, random sequence generation was not described; in the remaining trials, there was an adequate method. In 22 trials, the method of allocation concealment was not described; in three trials, allocation was clearly not concealed; and in 20 trials, allocation concealment was adequate. Therefore, a high risk of selection bias was likely in over 50% of trials.
Blinding of participants and the care providers was not possible, so performance bias was likely; however, outcome assessors can be blinded. For 13 trials where the outcome data were obtained by interview, 5 described the rater as blind, 3 as not blind and 5 had no description. In nine trials, the outcome was obtained from medical records; in five of these the rater was blind, in two not blind and it was unclear in two trials. In 13 trials, interview and medical records were used to obtain the outcome; in seven of these the rater was blind, in one not blind and in five it was unclear. In one trial, self-harm data were collected via the National Surveillance system and there was no description of blinding. In four trials, it was not clear how the outcome data were obtained; in one of these trials, the rater was blind. In three trials, self-harm outcomes were collected by self-report questionnaire and therefore cannot be blind. In two studies, self-harm outcomes were not collected. Detection bias was therefore likely in over 50% of trials.
Nineteen trials were rated as being with a low risk of bias with <15% lost to follow-up or missing outcome data. There was a high rate of missing data in 19 trials (>15%) and in only 11 was an ITT analysis described; the amount of missing data was unclear in six trials and in only one of these was an ITT analysis described. Therefore, eight trials were rated as being of a high risk of bias, and 17 as unclear so that attrition bias was present or likely in 55.5% of trials (see table 1 for a description of each trial and figure 2 for a summary graph of the risk of bias).
Summary graph of review authors’ judgements about each risk of bias item presented as percentages across all included studies.
Synthesis of results: meta-analyses
Primary outcome
The proportion of individuals with any repeat episode of self-harm after an intervention ranged from 0% to 55% in the intervention arm, and from 0% to 71% in the control arms.
Participants in the psychological or psychosocial interventions (combined) group had 0.84 times the risk of any further episode of self-harm relative to those in the comparator conditions (36 trials; 7354 participants, 95% CI 0.74 to 0.96; p=0.01; I2 33%). This effect translates to an NNT of 33. There was evidence of an effect of CBT (5 trials, RR 0.77; 95% CI 0.64 to 0.93) and psychodynamic interpersonal psychotherapy (1 trial; RR 0.31; 95% CI 0.12 to 0.78) in reducing the rate of repetition compared to comparator conditions. There was no strong evidence that complex interventions with outreach (13 trials, RR 0.90; 95% CI 0.73 to 1.11), problem-focused interventions (8 trials, RR 0.96, 95% CI 0.80 to 1.16), interventions classed as other-psychological (4 trials, RR 0.91; 95% CI 0.39 to 2.11) or interventions classed as other-psychosocial (5 trials, RR 0.86; 95% CI 0.58 to 1.27) had an effect on reducing rates of repetition of self-harm (see figure 3).
Forest plot of any psychological or psychosocial intervention versus control for self-harm.
The direction of effects across trials indicated that some study-specific effect estimates fell within benefit and some fell within harm.
Secondary outcomes
There was strong evidence that compared with any type of comparator condition, psychological or psychosocial interventions (combined) were associated with reduced severity of suicidal ideation (36 trials, SMD −0.42; 95% CI −0.60 to −0.25; p<0.00001; I2=64%), depressive symptoms (36 trials, SMD −0.23; 95% CI −0.36 to −0.10; p=0.0003; I2=57%) and hopelessness (34 trials, mean difference of −1.47; 95% CI −2.16 to −0.78; p<0.0001; I2=34%; all trials used the Beck Hopelessness Scale, which has a score range of 0–20).
Additional analyses: sensitivity analyses
Excluding trials rated as being of a high or unclear risk of bias for allocation concealment and, in a second sensitivity analysis, for outcome rater blinding showed that there was no longer strong evidence for reduction in risk of any self-harm event for concealment (20 trials: RR 0.94; 95% CI 0.83 to 1.06, I2=22%) and for blinding (16 trials: RR 0.84; 95% CI 0.70 to 1.02, I2=34%).
Additional analyses: meta-regression
Moderating variables: intervention approach and components
Neither the type of intervention, nor the intensity of the intervention nor any of the other binary components of the intervention investigated had any association with the magnitude of the intervention effect (p=0.365) (table 2).
Effects of single covariates for meta-regression of all trials of psychological or psychosocial intervention versus comparator
Moderating variables: aspects of methodology
The sample size of a trial appeared to have a weak association with the magnitude of the effect (RR=1.0006, p=0.046) (see table 2) and when the sample size of each intervention was entered in the meta-regression model (k=36), the I2 value reduced to 22%. There was no significant association between the type of comparator (TAU, TAU+ or an alternative active control intervention) or participant population (ie, on the basis of self-harm, suicide attempt or self-poisoning) and the magnitude of intervention effect.
Assessment of reporting bias
There was some evidence that there were missing studies (see online supplementary figure S1).
supplementary figure
Funnel plot of trials comparing any psychological or psychosocial intervention with any comparison condition for repetition of self-harm
Discussion
Principal findings
We included 45 trials of psychological and psychosocial interventions to prevent repeat self-harm and examined the type of intervention and components of interventions that were potential modifiers of overall efficacy. There were three main results from 36 of these trials: (1) there is evidence that any kind of psychological or psychosocial intervention (when combined) aimed at reducing a repeated episode self-harm had a protective effect that represents an important public health impact and is potentially clinically relevant at an individual level compared to any comparator condition; (2) there currently is no strong evidence that the type of intervention modifies overall efficacy; and (3) there was strong evidence of benefits of any kind of psychological or psychosocial interventions on the severity of suicidal ideation, depression symptoms and hopelessness scores. The effects appear to be small, but may be clinically important.
A change in clinical practice is warranted
Any repeat episode of self-harm is a difficult outcome to influence, in part because it occurs in a minority; most will not repeat after 12 months even without intervention. However, because of the high prevalence of self-harm with a repetition rate of around 16% at 12 months,1 even small beneficial effects will be important at the public health level. The benefit for a clinician considering treatment for an individual patient is not as clear-cut. The relative reduction of 16% for a repeat self-harm event is small, with an absolute risk reduction of around 3% (16–13%). Nonetheless, this reduction translates to an NNT of 33, the same as for a Cochrane review of interventions for the prevention of depression;88 and much better than well-accepted interventions, for example, aspirin to prevent a cardiovascular event NNT of 28489 and antihypertensive medications for those with high blood pressure to prevent a stroke NNT of 169.90 From the clinician's viewpoint, there were also benefits on suicidal ideation, depression and hopelessness. Using Cohen's rule, these differences are small but may not be trivial, particularly because severity of suicidal ideation is associated with the risk of suicide attempt.91 ,92
It would be worthwhile for clinicians treating patients who have presented to hospital with self-harm to consider a psychological or psychosocial intervention; with the best choices being CBT or, based on one trial to date, psychodynamic interpersonal therapy. This is consistent with the NICE guidelines for after-care recommending that clinicians ‘consider offering 3 to 12 sessions of a psychological intervention that is specifically structured for people who self-harm’.27
Potential cost savings
There have been no cost-effectiveness or cost-utility analyses for psychosocial interventions aimed at reducing repetition of self-harm; and now that overall clinical benefit has been demonstrated to be possible, we expect that these analyses should be incorporated into future well-designed studies. There have also been only infrequent analyses of improved opportunity costs to the health system, based on reduced admission rates or length of stay for self-harm interventions.93 However, before any intervention can be considered to be scaled up for widespread availability, the prospect of direct and substantial cost savings to the health system needs to be demonstrated. To illustrate this point, we have made some speculative calculations about possible direct cost savings.
For England, the annual number of hospital-treated self-harm events is ∼220 000,94 with a third (73 333) likely to be repeat events; so providing intervention could potentially avoid 2200 events (by reducing the risk of repetition in this group from 16% to 13%). Assuming 90% of these require ambulance transport (cost £24695 per trip; savings £487 080), 100% attend emergency department (£110 per attendance;95 savings £242 000) and 60% are admitted (£204–£4231per admission;95 midpoint cost of £2217; savings £2 926 440), this is a potential savings of around £3 655 520 per year. For Australia, based on sentinel service monitoring,96 the scaled up annual national number of hospital-treated self-poisoning events is 79 920; a third are estimated repeat events, with around 800 hospital presentations potentially avoided. Hospital treatment costs are $A301597 (without complication) or $A853497 (with complications); at a ratio of 6:1,98 this is a potential cost savings of $A3 041 166 per year.
Strengths and limitations
This review has significantly updated the evidence base by identifying 45 relevant RCTs undertaken in self-harm populations; this is the largest number of psychological and psychosocial trials identified in a systematic review. We have not included brief contact interventions (summarised elsewhere16), nor investigated the effectiveness of interventions for specific targeted subpopulations, such as those with BPD or psychosis, therefore no trials of DBT, mentalisation or schema-focused therapy are included. It should also be noted that the majority of trials were undertaken in populations who presented to a general hospital and many people who engage in self-harm do not present in this way.
Our review adopted robust systematic review methodology, including analysis of meaningful secondary outcomes, sensitivity analysis to assess the impact of risk of bias on the results and analyses that examined whether the type of intervention modified the intervention effect. Nevertheless, the results of the meta-analysis and meta-regression in this review should be treated with some caution given that the risk of bias in various domains was rated as high. When poorer quality trials (those with a high risk of bias with regard to allocation concealment, and separately for outcome assessor blinding) were excluded from the analysis in sensitivity analysis, there was no strong evidence of the effect of the interventions on repetition of self-harm, although it may be that the analysis was then limited in terms of power. We noted significant limitations in the reporting of the nature of psychological and psychosocial interventions delivered and point to the template for intervention description and replication (TIDier) guidelines for reporting of interventions.99 There were few trials in some categories of intervention type, limiting the power to investigate whether the type of intervention modifies the overall intervention effect. This requires further investigation. Given the relatively small number of trials, we did not have the data to enter all the multiple confounders into the same analysis or test interactions. It should be noted that there is diversity in terms of the populations included, for example, social context, the types of interventions (we have focused our attention on a number of confounders with regard to this diversity) and methodological factors, for example, Zelen versus conventional randomisation. Therefore, it is possible that the variation in intervention effects can be explained by other, or a combination of variables. In terms of the meta-regression, the results are observational in nature and cannot infer causality (ie, the effect seen may be due to a third factor); as such they are considered to be hypothesis generating rather than providing robust conclusions.100
There is little information available about treatment costs or cost-effectiveness for any after-care intervention. We have not investigated other important self-harm outcomes, such as time to first repeat self-harm episode or number of repetition events; and few if any studies report adverse events, which would also assist the clinician in decision-making about treatment options.
Implications and future research
The trials in this meta-regression included unselected populations of participants who had recently engaged in self-harm where the most common reasons for hospital presentation are interpersonal and social problems.101 Therefore, psychological and psychosocial therapies focusing on proximal interpersonal issues are plausible, and the single trial of four sessions of psychodynamic-influenced interpersonal therapy55 fits this approach. This trial has not been replicated and this type of therapy warrants a future large-scale trial. Hospital-treated self-harm populations are heterogeneous in terms of psychiatric diagnosis and life problems. The way forward might be to develop targeted interventions for clinically important subpopulations classified by age, gender, life problem, substance misuse or other criteria in line with the needs-based approach to assessment and after-care as recommended by the NICE guidelines.102 Future interventions to be developed and evaluated might contain particular elements: CBT based, with an interpersonal focus targeted on the psychosocial precipitants to the self-harm event.
Conclusions
Our study is consistent with the updated Cochrane review,14 which in contrast to the original version5 showed no support for problem-focused (predominantly problem-solving therapy) interventions but a significant effect of CBT. The updated Cochrane review14 and other reviews18 ,19 ,96 have shown DBT to be effective for patients with BPD;18 ,19 ,96 similarly brief contact interventions are promising for unselected self-harm patients.16 Our study has shown that psychological or psychosocial interventions are effective overall, with CBT and psychodynamic interpersonal therapy currently the most promising for implementation.
Acknowledgments
The study was conducted at Orygen, the National Centre of Excellence in Youth Mental Health and the Centre for Youth Mental Health at the University of Melbourne.
References
Footnotes
Contributors All authors have contributed substantially to the systematic review, analyses included in it and in the write-up of the manuscript. GC and SEH conceived of the study and developed the protocol; SEH and JR selected studies for inclusion and extracted data; SEH, GC and MJS did the analyses; SEH prepared the manuscript with input from all authors.
Funding This research received no specific grant from any funding agency in the public, commercial or not-for-profit sectors.
Competing interests GC chaired the Royal Australian and New Zealand College of Psychiatrists Clinical Practice Guidelines for Deliberate Self-harm, but the views in this paper are the author's own and not those of the RANZCP. SEH and JR are authors for the Royal Australian and New Zealand College of Psychiatrists Clinical Practice Guidelines for Deliberate Self-harm but the views in this paper are the author's own and not those of the RANZCP. All authors have completed the Unified Competing Interest form at http://www.icmje.org/coi_disclosure.pdf (available on request from the corresponding author) and declare that SEH, JR, MJS and GC do not have any support from any organisation for the submitted work; SEH, JR, MJS and GC have no financial relationships with any organisations that might have an interest in the submitted work in the previous 3 years; neither do their spouses, partners or children have any financial relationships that may be relevant to the submitted work; and SEH, JR, MJS and GC do not have any other relationships or activities that could appear to have influenced the submitted work. All authors have seen and approved the manuscript being submitted. They warrant that the article is the authors' original work, has not received prior publication and is not under consideration for publication elsewhere.
Provenance and peer review Not commissioned; externally peer reviewed.
Data sharing statement No additional data are available.