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Selecting Suicide Ideation Assessment Instruments: A Meta-Analytic Review

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Title: Selecting Suicide Ideation Assessment Instruments: A Meta-Analytic Review
Language: English
Authors: Erford, Bradley T., Jackson, Jessica, Bardhoshi, Gerta, Duncan, Kelly, Atalay, Zumra
Source: Measurement and Evaluation in Counseling and Development. 2018 51(1):42-59.
Availability: Routledge. Available from: Taylor & Francis, Ltd. 530 Walnut Street Suite 850, Philadelphia, PA 19106. Tel: 800-354-1420; Tel: 215-625-8900; Fax: 215-207-0050; Web site: http://www.tandf.co.uk/journals
Peer Reviewed: Y
Page Count: 18
Publication Date: 2018
Document Type: Journal Articles
Information Analyses
Reports - Research
Descriptors: Suicide, Psychological Patterns, Meta Analysis, Evaluation Methods, Screening Tests, Rating Scales, Questionnaires, Intention, Test Validity, Test Reliability, Probability, Risk, Literature Reviews
DOI: 10.1080/07481756.2017.1358062
ISSN: 0748-1756
Abstract: Psychometric meta-analyses and reviews were provided for four commonly used suicidal ideation instruments: the Beck Scale for Suicide Ideation, the Suicide Ideation Questionnaire, the Suicide Probability Scale, and Columbia--Suicide Severity Rating Scale. Practical and technical issues and best use recommendations for screening and outcome research are offered.
Abstractor: As Provided
Number of References: 135
Entry Date: 2018
Accession Number: EJ1169520
Database: ERIC
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  Value: <anid>AN0127116368;mev01jan.18;2018Jan09.13:10;v2.2.500</anid> <jsection id="AN0127116368-1"> APPLICATIONS OF ASSESSMENT</jsection> <title id="AN0127116368-2">Selecting Suicide Ideation Assessment Instruments: A Meta-Analytic Review </title> <p>Psychometric meta-analyses and reviews were provided for four commonly used suicidal ideation instruments: the Beck Scale for Suicide Ideation, the Suicide Ideation Questionnaire, the Suicide Probability Scale, and Columbia- Suicide Severity Rating Scale. Practical and technical issues and best use recommendations for screening and outcome research are offered.</p> <p>Keywords: Meta-analysis; suicide assessment; suicide ideation</p> <p>Suicide ideation is common, with a lifetime prevalence of over 10% in the U.S. population; thus, suicide ideation is an important determinant of suicide risk and one that requires appropriate intervention (Nock et al., 2013). Suicide was the 10th leading cause of death in individuals of all ages in the United States in 2012 and resulted in an estimated $34.6 billion in lost work and medical costs per year. Gender differences exist among those completing suicides with males accounting for 79% of all suicides, making males four times more likely than females to complete a suicide; at the same time, females are far more likely to attempt suicide (McIntosh & Drapeau, 2014).</p> <p>Differences in suicide completion by age also exist. Suicide is the second leading cause of death among adults aged 25 to 34 years of age and the third leading cause among those aged 15 to 24 years. Among males, suicide rates are highest for those aged 75 years and over. Racial and ethnic disparities also affect suicide, with higher suicide rates recorded for American Indians and Alaska Natives than other ethnicities, nearly 2.5 times higher than the national average suicide rate among the 15-to 34-year-old age group (Centers for Disease Control and Prevention, 2012).</p> <p>Individuals with an acute risk of suicidal behavior often show signs that can alert professionals and nonprofessionals alike. Although long-term suicide risk factors encompass biological, emotional, and environmental domains (Erford, 2013), presentation of suicidality might first be indicated by imminent warning signs. The threat of harm to self, seeking access to lethal means such as weapons or pills, or communicating through writings, social media, or songs about death and dying are important warning signs. Drastic changes in mood, acts of recklessness or aggression, withdrawal from relationships, and increased substance use might also indicate imminent risk (Chesin & Stanley, 2013). Suicidal risk also increases the probability of cooccurrence with a variety of mental disorders such as depression, bipolar, anxiety, eating, trauma-related, and adjustment disorders (Seligman & Reichenberg, 2012). Unfortunately, even when individuals who have attempted suicide in the past year receive mental health care, approximately half report unmet treatment needs, further increasing risk for reattempts and completion (Han, Compton, Gfroerer, & McKeon, 2014).</p> <p>Suicidal ideation is commonly encountered by mental health professionals working with adolescents and adults, and assessment and treatment of these individuals can be very stressful (Granello & Granello, 2007). Although clinical interviews are almost always used for assessment of suicidal ideation, there is no literature specifying how frequently standardized suicide assessment instruments are used in clinical practice, or under what conditions the instruments are used. This leads to the question of whether integration of standardized instruments in conjunction with clinical interviews could lead to better practices and triangulation of results from multiple sources.</p> <p>Although there are a variety of instruments useful for assessing suicidal risk, little is known about the psychometric integrity of these standardized instruments other than what is published in the test user manuals and scattered throughout the literature in individual articles. The purpose of this article was to provide a comprehensive synthesis of psychometric evidence from the extant literature to evaluate, compare, and contrast four of the most commonly used and cited standardized suicide ideation instruments: the Beck Scale for Suicide Ideation (BSS; Beck & Steer, 1991), the Suicide Ideation Questionnaire (SIQ; Reynolds, 1988), the Suicide Probability Scale (SPS; Cull & Gill, 1992); and the Columbia-Suicide Severity Rating Scale (C-SSR; Columbia University, 2014). A discussion of practical issues, technical strengths and weaknesses, and best use recommendations for screening and counseling outcome research will inform clinicians and researchers on the selection process of suicide ideation assessment instruments. Furthermore, frequency of use of these instruments in suicide research could inform counselors of the relative usefulness of these instruments in clinical practice.</p> <hd id="AN0127116368-3">Methodological Considerations</hd> <p>The psychometric meta-analytic results that follow were derived from journal articles, dissertations, and other electronically available sources that met the following criteria: (a) used the English version of the main instrument (other language translations and brief or modified versions are designated as such and presented separately, as appropriate); and (b) provided some type of reliability, validity, or nonconclinical sample mean data. Foreign language translated versions were not aggregated with English language versions because they generally did not conform to best practices translation procedures (AERA/APA/NCME, 2014, Standard 9.7). The studies included in this meta-analysis were independent of the standardization samples or studies reported in the manual or issued by the instrument authors when providing initial psychometric evidence for instrument use.</p> <p>Redundant search procedures were undertaken to identify candidate studies. Electronic searches were followed by hand searches of synthesis and selected article reference lists. PsychINFO, ERIC, Academic Search Premier, Cochrane Central Register of Controlled Trials, and MEDLINE articles for the year of and subsequent to publication of each instrument were included, inclusive of 2015. Keywords included the instrument name and acronym (e.g., Beck Scale for Suicide Ideation and BSS) for full-text search. Additional candidate studies were then located by searching the reference lists of the selected articles and synthesis studies. Full-text versions of each candidate article were inspected, selection criteria applied, and all articles meeting the selection criteria were included in the analysis.</p> <p>The primary variables of interest in each instrument psychometric meta-analysis were internal consistency (α), test-retest reliability (r<subs>tt</subs>), convergent correlations (r) with other suicide ideation or related measures (e.g., depression, hopelessness), structural validity (i.e., exploratory factor analysis [EFA], confirmatory factor analysis [CFA]), diagnostic validity (e.g., percent of correct classifications, sensitivity, specificity, positive predictive power, negative predictive power, area under the curve [AUC] estimates), and descriptive statistics (i.e., means and standard deviations) from nonclinical samples for use in norms comparisons. Sample size weightings for α and r<subs>tt</subs> coefficients were applied directly. All convergent coefficients (r) were independent and corrected for sampling bias by first transforming r into z values (½log[?????]; Hedges & Olkin, 1985), then weighed by sample size, summed, averaged, and the grand z back-transformed to r. The 95% CI (indicated in brackets [] throughout this article) was calculated to test the null hypothesis of r = 0; the null was rejected if the entire 95% CI was > 0.</p> <hd id="AN0127116368-4">Review and Comprehensive Psychometric Meta-Analysis of the Beck Scale for Suicide Ideation</hd> <p>The BSS is a self-report instrument used to identify and measure suicide ideation among adolescents and adults (Beck & Steer, 1991). The BSS was developed as a self-report version of the clinician-report Scale for Suicide Intention (SSI; Beck, Kovacs, & Weissman, 1979). The BSS contains 21 clusters of statements with each containing three statements marked 0, 1, or 2. Statements designated with 0 indicate low suicide ideation and statements designated with 2 indicate high suicide ideation. The 21 statements are broken down into two parts. Part 1 measures the clients' desire to live or die, their reasons for living or dying, and their ideation of active or passive suicide attempts. If the client chooses the 0 statements on Clusters 4 and 5, they proceed to Cluster 20 and 21, designed to measure their past suicide behavior. If they choose the 1or 2 statements on Clusters 4 and 5, they move on to Cluster 6 and complete the test in order, where factors such as duration and frequency of ideation, deterrents and reasons for attempts, and deception and concealment are measured.</p> <p>Administration requires only 5 to 10 minutes and can be completed independently by the client, or the examiner could read the scale aloud and mark the responses for the client. This level C instrument (Erford, 2013) should be scored by professionals with clinical training and experience, as the professional might need to provide an appropriate therapeutic or crisis response based on the examinee's score (Beck & Steer, 1991). The BSS is scored by adding the raw score points from the selected statements (0, 1, or 2). Total scores can range from 0 to 38 and there is no suggested criterion-related cutoff score. Indeed, any positive response to any BSS item could reveal the presence of suicide intention and should be carefully investigated by the clinician.</p> <p>The BSS was developed for use with both inpatient and outpatient adult psychiatric clients and was standardized on a group of 50 inpatients and 55 outpatients from a suburban general hospital (Beck, Steer, & Ranieri, 1988) with 46% of participants describing prior suicide attempts. Cronbach's coefficient α for the subgroups of inpatient and outpatient suicide ideators was .90 and .87, respectively. One-week test-retest stability was also studied on 60 inpatients, but was found to be low (r = .54), probably due to the clinical improvement expected after a week-long hospitalization treatment regimen. Scores on the BSS correlated significantly with scores on the SSI (Beck, Kovacs, & Weissman, 1979; r = .90), Beck Depression Inventory (BDI; Beck, Steer, & Brown, 1996; r = .64), and Beck Hopelessness Scale (BHS; Beck & Steer, 1993; r = .53).</p> <p>The standardization sample was not very diverse and additional studies on the effectiveness of the BSS with minorities are needed. The BSS has been translated into many languages, including Spanish, Urdu, Farsi, Portuguese, Brazilian, and Norwegian. Additional studies have explored test validity and reliability for use with inpatient populations diagnosed with schizophrenia, schizoaffective, or bipolar disorder (Pinninti, Steer, Rissmiller, Nelson, & Beck, 2002), inmates (Way, Kaufman, Knoll, & Chlebowski, 2013), people with sex disorders (Schützmann, Brinkmann, Schacht, & Richter-Appelt, 2009), and with a nonclinical population of university students using the Norwegian language version (Chioqueta & Stiles, 2006), among others.</p> <p>Of candidate articles available from 1993 through 2015, 420 were identified through computerized and hand searches. Full-text review of all candidate articles eliminated 413 articles for violating one or more of the inclusion criteria. Thus, only seven (j = 7) articles with a combined sample size of 1,059 participants were analyzed. Two studies reported as (Bisconer & Gross, 2007; Steer, Rissmiller, Ranieri, & Beck, 1993), combining for a grand a of .91 (.81-1.00; n = 397), consistent with the .90 and .87 reported by Beck and Steer (1991) for inpatient and outpatient samples, respectively. No test-retest studies were located in the literature. Concurrent validity comparisons (see Table 1) showed strong correlations between the BSS and the C-SSR (Posner et al., 2011; n = 472, r = .52), SPS (Cull & Gill, 1992; n = 67, r = .65), and Adult Suicide Ideation Questionnaire (ASIQ; Reynolds, 1988; n = 67, r = .64). Interestingly, anxiety (Beck Anxiety Inventory [BAI]; Beck, 1993; n = 122, r = .55) was just as highly correlated as the suicide-related constructs of depression (BDI; Beck, Steer, & Brown, 1996; n = 535, r = .58) and hopelessness (BHS; Beck & Steer, 1993; n = 406, r = .55).</p> <p>One EFA was located (Steer, Rissmiller, Ranieri, & Beck, 1993) with an appropriately powered sample size of 330 psychiatric outpatients. A principal factor analysis with promax rotation generated a three- factor solution on which all but six items loaded significantly. Factor I, desire for death, was composed of Items 1, 2, 3, 5, and 8; Factor II, preparation for suicide, was composed of Items 12 to 18; and Factor III, active suicidal desire, was composed of Items 4, 6, 7, and 9. These three factors were strongly intercorrelated (r = .50-.62). No CFAs were located, so the Steer et al. (1993) study provides the only evidence of internal structural validity on the BSS.</p> <p>One study was located yielding evidence of diagnostic validity (also known as decision reliability; see Erford, 2013) on the BSS (Cochrane-Brink, Lofchy, & Sakinofsky, 2000). At a recommended cutoff score of ≥ 24 raw score points, sensitivity = 1.00, specificity = .90, positive predictive power = 1.00, and negative predictive power = .72, with an overall accuracy rate of close to 95%. These were quite impressive and robust results. A second study was located that provided evidence for a 5-item short form version of the BSS (Koldsland, Mehlum, Mellesdal, Walby, & Diep, 2007), concluding that a cutoff score of ≥ 1 was optimal, yielding sensitivity = .80, specificity = .78, positive predictive power = .77, and negative predictive power = .40, with an overall accuracy rate of close to 79%. These results were less promising, so clinicians and researchers will likely obtain more accurate hit rates using the full version of the BSS. Finally, no study statistics were reported for nonclinical samples on the English version of the BSS that could be used to estimate sample norms, although Ekramzadeh et al. (2012) reported a mean of 1.69 (SD = 2.25, n = 650) for a Farsi translation of the BSS, and Alexandrino-Silva et al. (2009) reported a mean of 0.38 (SD = 1.50, n = 987) for a Portuguese translation of the BSS on a sample of Brazilian medical students.</p> <hd id="AN0127116368-5">Review and Comprehensive Psychometric Meta-Analysis of the Suicide Ideation Questionnaire and Junior High Version</hd> <p>The SIQ and SIQ-JR (Junior High version) measure the multifaceted concept of suicide ideation in adolescents (Reynolds, 1988), and attempt to address the lack of appropriate screening for suicide ideation in adolescence. The SIQ contains 30 items and the SIQ-JR contains 15 items. The client responds to each item on a 7-point scale (i.e., 0-6) according to the temporal frequency of the agreement with the item in the past month. Responses range from I never had this thought to almost every day and include I had this thought before but not in the past month. Both versions can be administered individually, or in small or large groups. The SIQ scores are calculated by summing the raw scores for each item. Scores from 0 to 180 are possible on the SIQ and from 0 to 90 on the SIQ-JR, with higher scores indicating more severe suicide ideation. Respondents with a raw score of 41 or above on the SIQ, or 31 or above on the SIQ-JR, should be further evaluated for suicide risk and potentially significant psychopathology. Scores of critical items identified by Reynolds through theoretical means (as opposed to empirical means) can be listed as well, as they might indicate the potential for serious self-harm behavior (Reynolds, 1988). Those items are 2, 3, 4, 7, 8, 9, 13, and 18 on the SIQ and 2, 3, 4, 7, 8, and 9 on the SIQ-JR. Scores on two or more of these specific items indicating that these thoughts occur a "couple of times a week" or "almost every day" should be taken seriously regardless of overall score.</p> <p>Reynolds (1988) reported an internal consistency reliability coefficient of .97 for the SIQ and .94 for the SIQ-JR. Although suicidal ideation is not considered a stable mental state, 4-week test-retest reliability of the SIQ (n = 801) was .72. The scores of the SIQ and SIQ-JR were quite consistent with scores on the Reynolds Adolescent Depression Scale (RADS; Reynolds, 2002; r ranging from .55-.63), the BDI (Beck, Steer, & Brown, 1996; r = .53) and Children's Depression Inventory (CDI; Kovacs, 1992; r ranging from .65-.70), and the BHS (Beck & Steer, 1993; r = .47). The SIQ and SIQ-JR have been used on diverse populations, including adolescents with behavioral disorders, clinical adolescent populations (Pinto, Whisman, & McCoy, 1997), and female college students 18 and 19 years old (Klosterman-Fields, 1985). The SIQ has also been expanded for use with adults (ASIQ; Reynolds, 1991) and published in other languages including Chinese (Zhang, Yip, & Fu, 2014), French (Potard, Kubiszewski, Gimenes, & Courtois, 2014), Korean, Arabic, and Afrikaan (South Africa).</p> <p>Of candidate articles, 125 were identified through computerized and hand searches and full-text review eliminated all but 35 articles for a combined sample size of 10,942 participants. Internal consistency estimates of the SIQ were provided in 14 articles (Abdel-Khalek & Lester, 2007; Chang, 2002; Cross, Cassady, & Miller, 2006; Gencoz, Vatan, Walker, & Lester, 2007; Gutierrez, Osman, Barrios, & Kopper, 2001; Horesh & Apter, 2006; Lynch, Cheavens, Morse, & Rosenthal, 2004; Miller & Esposito-Smythers, 2013; Osman et al., 1999; Pieneer, Rothman, & Van De Vijver, 2007; Pinto, Whisman, & McCoy, 1997; Reynolds, 1991; Steyn, Vawda, Wyatt, Williams, & Madu, 2013; Walker, Lester, & Joe, 2006) for a combined sample of 5,858 participants yielding an average α = .95 [.92, .98], a very high coefficient. A single test-retest reliability study was reported, and using a 1-week interval derived r<subs>tt</subs> = .86 [.77, .95] (n = 474; Reynolds, 1991). An additional three articles exploring the internal consistency of a Korean translation of the SIQ were also located and reported a combined α = .97 [.90, 1.00] (n = 751; J. Lee, Choi, Kim, Park, & Shin, 2009; S-Y. Lee, 2011; Shin, 1992).</p> <p>Concurrent validity coefficients (see Table 1) were robust with other measures of suicidal ideation, such as the Suicide Opinion Questionnaire (SOQ; Domino, Moore, Westlake, & Gibson, 1982; j = 1, n = 81, r = .70 [.48, .92]; Lester, 2004). Resilience to suicide was compared with the Suicide Resiliency Inventory (SRI-25; Osman et al., 2004; j = 1, n = 239, r = -.67 [-.54, -.80]; Rutter, Freedenthal, & Osman, 2008) and the Reasons for Living Inventory (RFL; Linehan, Goodstein, Nielsen, & Chiles, 1983; j = 1, n = 320, r = -.66 [-.55, -.77]; Kumar, Atanu, Basu, & Das, 2008). Depression inventories, such as the BDI (Beck, Steer, & Brown, 1996; j = 3, n = 1,030, r = .58 [.52, .64]; Chang, 2002; Reynolds, 1991; Weber, Metha, & Nelson, 1997), RADS (Reynolds, 1987; j = 1, n = 151, r = .47 [.31, .63]; Spirito, Sterling, Donaldson, & Arrigan, 1996), and Minnesota Multiphasic Personality Inventory (MMPI; Butcher, Dahlstrom, Graham, Tellegen, & Kaemmer, 1989) Depression subscale (j = 1, n = 118, r = .64 [.46, .82]; Osman et al., 1999) were moderately correlated. Hopelessness inventories such as the BHS (Beck & Steer, 1993; j = 4, n = 1,485, r = .50 [.45, .55]; Gencoz et al., 2007; Lynch, Cheavens, Morse, & Rosenthal 2004; Reynolds, 1991; Weber et al., 1997) and Hopelessness Scale for Children (HSC; Kazdin, Rodgers, & Colbus, 1986; j = 1, n = 151, r = .49 [.33, .65]; Spirito et al., 1996) also yielded moderate correlations with the BSS.</p> <p>Only one EFA for the SIQ was located. Abdel-Khalek and Lester (2007) reported a five-factor solution using principal components analysis (PCA) with a varimax rotation on a sample of 273 English- speaking undergraduates in Kuwait. In the same article they found a highly similar factor solution on an Arabic translation of the SIQ on scores from a sample of 460 Kuwaiti undergraduates. No CFAs of the SIQ were located. Only one decision reliability study was published using the SIQ. Pinto et al. (1997), on a sample of 226 adolescents, presented the cutoff score of 30 for optimal percent of correct classification (72%) and sensitivity (.78, specificity = .65, positive predictive power = .73, negative predictive power = .72), along with a cutoff score of 35 for optimal specificity (.65, percent of correct classification = .70, sensitivity = .72, positive predictive power = .73, negative predictive power = .66). Osman et al. (1999) used the 25-item ASIQ in a diagnostic validity study with 205 adult psychiatric patients, reporting the cutoff score of 14 for optimal sensitivity (.96, specificity = .79, positive predictive power = .73, negative predictive power = .97), along with a cutoff score of 20 for optimal specificity (.92, sensitivity = .80, positive predictive power = .85, negative predictive power = .89).</p> <p>Descriptive statistics were reported for six nonclinical samples (Chang, 2002; Gencoz et al., 2007; Kumar et al., 2008; Pieneer et al., 2007; Reynolds, 1991; Weber, Metha, & Nelsen 1997) resulting in a total sample grand mean of 11.1 (SD = 15.8, n = 3,563). Two studies disaggregated the results by sex (Cross, Cassady, & Miller, 2006; Reynolds, 1991) resulting in a male grand mean of 11.5 (SD = 13.7) and female grand mean of 13.6 (SD = 13.8) in a relatively small sample size of only 389 participants. Clinicians should use caution when using cutoff scores, such as the published raw score cutoff of 31 (Reynolds, 1988) because it might overidentify women or underidentify men engaging in suicidal ideation. Using this data, a total sample grand mean and standard deviation of 11.1 (15.8) means that a cut score of 31 will identify about 10% of a population (z = 1.26) with suicidal ideation. When applied to the small sample gender differential studies, a cutoff score of 31 is likely to identify 10% of females (z = 1.26), but only 7.5% of males (z = 1.42). A cutoff score of 41 is likely to identify 2% of females (z = 2.00) and males (z = 2.15).</p> <p>A number of studies focused specifically on the SIQ-JR. Six studies (Ang & Ooi, 2004; Bergen, 1999; Diamond, Creed, Gillham, Gallop, & Hamilton, 2012; Huth-Bocks, Kerr, Ivey, Kramer, & Kins, 2007; Keane, Dick, Bechtold, & Manson, 1996; Reynolds & Mazza, 1999) combined to yield an overall average α = .93 [.87, .99] (n = 977). Test-retest reliability of the SIQ-JR was studied in two articles combining for a 1.5-month grand r<subs>tt</subs> = .74 [.62, .86] (n = 268; Kaminer, Burleson, Goldston, & Burke, 2006; Reynolds & Mazza, 1999). Not surprisingly, as the length of the retest interval increased, r<subs>tt</subs>, decreased. For example, Reynolds and Mazza (1999) reported an approximate 1-month r<subs>tt</subs> of .89 (n = 91), whereas Kaminer et al. (2006) reported a 2-month r<subs>tt</subs> of .66 (n = 177). A robust SIQ-JR concurrent validity comparison was reported with the Reynolds Suicidal Behaviors Interview (SBI; Reynolds, 1990) as five studies (Bergen, 1999; King, Hill, Naylor, Evans, & Shain, 1993; Prinstein, Boergers, Spirito, Little, & Grapentine, 2000; Reynolds, 1990; Reynolds & Mazza, 1999) combined (n = 690) to yield a weighted average r = .66 [.59, .73]. No EFA or CFA studies were located for the SIQ-JR.</p> <p>Two diagnostic validity studies were identified using the SIQ-JR and both adopted a similar cutoff score, even though two very diverse samples were used. Keane et al. (1996) assessed 163 Native American adolescents and used a cutoff raw score of 30 to correctly classify 85% of the sample (sensitivity = .80, specificity = .86, positive predictive power = .27, negative predictive power = .98). Using a clinical sample of 289 adolescents hospitalized for psychiatric issues Huth-Bocks et al. (2007) applied a cutoff score of 31 to produce an optimal sensitivity index of only .77 with a concomitant low specificity of .41. Raising the cutoff score to 34 led to an optimal accuracy rate of only about 65%, with more balanced sensitivity (.69) and specificity (.61) rates. Still, an overall accuracy rate of 65% is very low for use in a clinical population, particularly assessing suicide risk. Finally, descriptive statistics were reported for three nonclinical SIQ-JR samples (Kaminer et al., 2006; Keane et al., 1996; Reynolds & Mazza, 1999) resulting in a total sample grand mean of 10.0 (SD = 15.0, n = 431).</p> <hd id="AN0127116368-6">Review and Comprehensive Psychometric Meta-Analysis of the Suicide Probability Scale</hd> <p>The SPS (Cull & Gill, 1992) is a 36-item self-report measure designed to assess suicide risk in adolescents and adults. The SPS is quick and easy to administer to individuals and groups, taking about 5 to 10 minutes. Clients should be directed to indicate how often each statement applies to them on a 4-point scale, without being informed that the test assesses suicide. In fact, the measure does not mention suicide in its title. This is considered a level C test (Erford, 2013), requiring a professional with a doctoral degree or a clinical license possessing knowledge regarding suicide, clinical assessment, and the ethical knowledge to work with clients who might present at a high risk for suicide. The items are scored across four subscales: Hopelessness, Suicide Ideation, Negative Self-Evaluation, and Hostility. A total weighted score, suicide probability score, and a normalized T score are also generated, to facilitate a more in-depth interpretation of the scores. Thus, the SPS is the only instrument among the four reviewed in this article to yield norm-referenced interpretive scores. The SPS is easily scored by hand, but scoring is also available via Western Psychological Services (WPS) Test Report Fax service, which immediately provides users with scores and summaries in a single-page report.</p> <p>The SPS was normed on a sample of more than 1,000 individuals across the general population, psychiatric patients, and lethal suicide attempters. According to Cull and Gill (1992), the internal consistency (α) of the SPS total score was .93, and for the four subscale scores were: Hopelessness, .85; Suicide Ideation, .88; Negative Self-Evaluation, .58; and Hostility, .78. Test-retest reliability for the total score was also examined after 10 days (r<subs>tt</subs> = .94, n = 478).</p> <p>Computerized and hand searches identified 188 candidate articles for full-text review, with subsequent elimination of 150 articles that violated one or more inclusion criteria, leaving 38 articles to analyze with a total sample size of 9,254. Six of the eliminated articles provided usable results for foreign language versions of the SPS and are reported in context later. The SPS has been translated into Turkish, Korean, Swedish, and French.</p> <p>The SPS internal consistency was strong across 10 studies at α = .91 [.87, .95] (n = 2,154; Bisconor & Gross, 2007; Eltz et al., 2007; Gutierrez et al., 2001; Gutierrez et al., 2002; Morrison & O'Connor, 2008; O'Connor & Noyce, 2008; Rudd, Joiner, & Rumzek, 2004; Stewart, 2009; Tatman, Greene , & Karr, 1993; Ustad, 1998). Test-retest stability over a 1- to 3-month interval in two studies (Morrison & O'Connor, 2008; O'Connor & Noyce, 2008) was r<subs>tt</subs> = .71 [.60, .82] (n = 313). As can be seen in Table 1, the SPS displayed consistent convergent correlations with other instruments measuring suicidal ideation (SRI [Osman et al., 2004], r = -.54 [-.49, -.59], n = 1,543; BSI [Beck & Steer, 1991], r = .51 [.32, .70], n = 112) and depression (Center for Epidemiological Studies-Depression scale [CES-D; Radloff, 1977], r = .64 [.53, .75], n = 313; BDI [Beck, Steer, & Brown, 1996], r = .67 [.60, .74], n = 858; MMPI [Butcher et al., 1989] Depression subscale, r = .68 [.59, .77], n = 475).</p> <p>Two studies reported EFA results, but only one of these provided any valuable information. Tatman et al. (1993) performed a PCA with varimax rotation on 217 nonclinical adolescents, concluding the existence of three factors that were highly correlated (r = .79-.90): suicidal despair (18 items), angry frustration (13 items), and low self-efficacy (12 items). Eltz et al. (2007) administered the SPS to 226 adolescent psychiatric inpatients, but then proceeded to conduct EFAs on each of the original four SPS subscales. Two CFAs were located. Eltz et al. (2007) indicated that the four-factor model was confirmed but did not report fit statistics as evidence. Bagge and Osman (1998) also reported that the four-factor model fit the data best, but the fit statistics were very low (comparative fit index = .79; nonnormed fit index = .77), although the root mean square error of approximation (.06) indicted an adequate fit.</p> <p>Two studies of diagnostic validity have been published using the full SPS; the published recommended raw score cut1off is 78 (Cull & Gill, 1992). In a large sample study, Larzelere, Smith, Batenhorst, and Kelly (1996) assessed 855 adolescents at Boys Town. The SPS results provided extremely low sensitivity (.28) and positive predictive power (.09), but a very respectable specificity of .90, meaning that the SPS did a good job of identifying who would not attempt suicide, but a very poor job of determining who would attempt suicide. In a second study, Huth-Bocks et al. (2007) found an optimal balance of results using the cutoff score of 78, but only identified about 65% of cases correctly (sensitivity = .65, specificity = .64). A third study was located in which Anderson, Townsend, Everly, and Lating (1995) assessed only 52 patients, then selected the most highly correlated items from the original 36 SPS items to compose a brief scale composed of 10 items (<reflink idref="bib12" id="ref1">12</reflink>,<reflink idref="bib15" id="ref2">15</reflink>,<reflink idref="bib21" id="ref3">21</reflink>,<reflink idref="bib24" id="ref4">24</reflink>,<reflink idref="bib25" id="ref5">25</reflink>,<reflink idref="bib29" id="ref6">29</reflink>, 32, 33,<reflink idref="bib34" id="ref7">34</reflink>, &36) that resulted in 83% correct classifications. Although promising, it is important to point out that small sample results must be replicated on larger, diverse samples before accepted for clinical decision-making purposes.</p> <p>Means and standard deviations for nonclinical samples were reported in four studies (Bagge & Osman, 1998; Gutierrez et al., 2002; Kopper, Osman, & Barrios, 2001; Tatman et al., 1993), resulting in a grand mean for the total sample (n = 1,300) of 55.7 (SD = 11.0). This is a large sample and an important observation here is that a cutoff score of 78 would be almost exactly 2 SDs above the nonclinical participant mean, effectively identifying only the top 2% of the distribution. Interestingly, when disaggregated by sex, the male total sample mean (M = 55.0) and standard deviation (SD = 9.0) across three studies (n = 420; Bagge & Osman, 1998; Kaplan et al., 2007; Kopper et al., 2001) was slightly higher than the female (n = 421) mean (53.0; SD = 9.7). However, when the scores are projected out 2 SDs above the mean, the cutoff score at the 98th percentile is virtually identical: a raw score of 73, which is a 0.5 SD again lower than the published cutoff raw score of 78.</p> <p>A number of articles have been published that studied only the Suicide Ideation subscale of the SPS, which is frequently used as a brief version and outcome variable. Eight articles (Dear, 2000; Heisel, Flett, & Hewitt, 2003; O'Connor, Fraser, Whyte, MacHale, & Masterson, 2008; O'Connor, O'Connor, & Marshall, 2007; O'Connor, Smyth, Ferguson, & Caoimhe Williams, 2013; O'Connor, Whyte, et al., 2007; Rasmussen, O'Connor, & Brodie, 2008; Rasmussen et al., 2010) reported a combined and weighted α = .87 [.81, .93] (n = 1,165). O'Connor et al. (2008) and O'Connor, Whyte, et al. (2007) reported a combined 2-month test-retest coefficient (n = 504) of r<subs>tt</subs> = .43 [.34, .52], which was quite low. Concurrent validity studies using the Suicide Ideation subscale yielded a coefficient with the CES-D scale (Radloff, 1977) of .58 [.42, .74] (n = 143; Heisel et al., 2003), a combined and weighted correlation across seven studies using the BHS (Beck & Steer, 1993) of r = .60 [.54, .66] (n = 1,169; Heisel et al., 2003; O'Connor, Whyte, et al., 2008; O'Connor et al., 2013; O'Connor et al., 2007; Rasmussen et al., 2008; Rutter, 2006; Rutter & Soucar, 2002), and a correlation across five studies using the Hospital Anxiety and Depression Scale-Depression subscale (HADS-D; Zigmond & Snaith, 1983) of r = .47 [.40, .54] (n = 764; O'Connor et al., 2008; O'Connor et al., 2013; O'Connor et al., 2007; Rasmussen et al., 2010; Rasmussen et al., 2008).</p> <p>Nonclinical Suicidal Ideation subscale sample means for both sexes combined (n = 463) yielded a mean of 9.0 and standard deviation of 5.6 across two studies (O'Connor, O'Connor, et al., 2007; Rutter, 2006). No diagnostic validity studies using the SPS Suicidal Ideation subscale alone were located.</p> <p>Finally, several additional studies were located that used translated versions of the SPS and are reported here for convenience, even though they were not included in the English version identification and results process. Lee (2011) reported α for the Korean translation of the SPS to be .90 [.80,1.00] (n = 406), and a concurrent validity coefficient with the Reasons for Living Inventory (RFL; Guttierez et al., 2002) of r = -.54 [-.44, -.64]. Eskin (1993b) reported α for the Swedish translation of the SPS to be .87 [.60,1.00] (n = 52) and a 1-month test-retest reliability coefficient of .89 [.62,1.00] (n = 474). Finally, four studies of the Turkish translation of the SPS were located (Dilli, Dallar, & Cakir, 2010; Eskin, 1993a; Eskin, Ertekan, Dereboy, & Demirkiran, 2007; Zeyrek, Gencoz, Bergman, & Lester, 2009), resulting in a combined weighted α of .88 [.82, .94] (n = 1,240). Eskin (1993a) reportedal-month r<subs>tt</subs> of .95 [.64,1.00] (n = 41). Concurrent correlations with the Turkish SPS were -.42 [.29, .55] (n = 214) with the RFL (Dilli et al., 2010), .62 [.47, .77] (n = 180) with the BHS (Zeyrek et al., 2009), and .70 [.63, .77] (n = 805) with the CDI (Eskin et al., 2007).</p> <hd id="AN0127116368-7">Review and Comprehensive Psychometric Meta-Analysis of the Columbia-Suicide Severity Rating Scale</hd> <p>The C-SSR was designed to help predict suicidal behavior in adolescents and adults (Columbia University, 2014). It was created in response to a need for a more comprehensive assessment of critical behaviors that put clients at risk for suicidal behavior. The C-SSR is highly praised as a quick, easy, and comprehensive tool to identify clients across various populations for referral to a mental health professional due to high suicide risk. There are different versions of the scale, designed to fit different clients (e.g., general population, clinical population, pediatric population), and different situations (e.g., first visit, follow-up visit). Administrators read the questions aloud to the client and mark down the response according to whether or not the client has felt this way in his or her lifetime or in the past month. According to the responses, the administrator proceeds through the questions in order, or skips to the next section. The first part of the C-SSR determines if the client has suicidal ideation. If the client does, the second section of the C-SSR determines the severity of the suicidal ideation. The third section determines if the client has engaged in suicidal behavior in his or her lifetime or in the past 3 months, and whether or not these behaviors were interrupted by the client or by others. The last section of the C-SSR collects a brief history of suicide attempts, if applicable. This section asks for the date and a professional assessment of the client's most recent suicide attempt, most lethal suicide attempt, and initial or first suicide attempt. These attempts are classified by the administrator as having actual or potential lethality. Once completed, the C-SSR is scored, and the administrator can access resources and consult on the next appropriate course of action with the client. If the client responds positively to any item on the suicide ideation section (<reflink idref="bib15" id="ref8">15</reflink>), then he or she is identified as having suicide ideation. In the intensity of ideation section, clients rate their "lifetime most-severe ideation" and "recent most-severe ideation" on a scale from 1 to 5, where 1 is the least severe and 5 is the most severe. The scores from this section are then added to give an intensity score, ranging from 0 to 25. If the client responds positively to any item in the suicidal behavior section, then he or she is identified as having suicidal behavior.</p> <p>The C-SSR was standardized across three populations: adolescent suicide attempters (n = 124), depressed adolescents in a medication efficacy trial (n = 312), and adults presenting with psychiatric issues to an emergency department (n = 237). Using the data collected in a study of adolescent suicide attempters, the internal consistency of the intensity subscale of the C-SSR was α = .95, whereas the samples of adults with psychiatric issues and adolescents in the medication efficacy trial both produced much lower coefficient alphas (α = .73; Posner et al., 2011). Using the data collected from the other two populations, the internal consistency of the intensity subscales for both visits was moderate, with α = .73. Convergent and divergent validity were examined by comparing the scores between the worst-point score on the SSI (Beck, Kovacs, & Weissman, 1979) with the Severity subscale of the C-SSR (r = .52, n = 472), and the Intensity subscale of the C-SSR (r = .56, n = 487). There was a strong correlation between the C-SSR Severity subscale and the Montgomery- Asberg Depression Rating Scale (MADRS) (Montgomery & Asberg, 1979) suicidal ideation item (r = .63) and the BDI (Beck, Steer, & Brown, 1996) suicide item (r = .80). The C-SSR has been studied with different populations, including adolescents in the juvenile justice system (Kerr, Gibson, Leve, & DeGarmo, 2014), and suicidal patients receiving depression interventions who were evaluated for efficacy (Hesdorffer et al., 2013; Wang et al., 2013), and has been translated into many different languages for use in 114 different countries (Columbia University, 2014).</p> <p>Computerized and hand searches identified 148 candidate articles submitted to full-text review, resulting in only 3 usable articles with a combined sample size of 917. Combined internal consistency across three samples from the Posner et al. (2011) articlewas only α = .84 [.78, .90] (n = 917), which is adequate for screening-level purposes (Erford, 2013), but far lower than the other three instruments reviewed earlier. Brent et al. (2009) reported test-retest reliability separately for the suicidal ideation items (r<subs>tt</subs> = .90 [.79, 1.00], n = 334) and suicidal behavior items (r<subs>tt</subs> = 1.00 [.89, 1.00], n = 334), coefficients that are very respectable, and higher than a. Posner et al. (2011) reported significant concurrent validity correlations between the C-SSR and the SIQ-JR (Reynolds, 1988; j = 1, n = 234, r = .36 [.23, .39]), BSS (Beck & Steer, 1991; j = 2, n = 683, r = .58 [.51, .65]), and Beck Lethality Scale (Beck, Shuyler, & Herman, 1974; j = 1, n = 234, r = .79 [.66, .92]). No EFA or CFA evidence, or descriptive statistics on nonclinical samples, was provided in the literature. Finally, Posner et al. (2011) reported diagnostic validity evidence in two studies using several cutoff schemes and resulting in perfect prediction of sensitivity (1.00) and near-perfect specificity predictions (.96-1.00), the best of any of the four instruments included in this analysis. Although decision reliability is the most essential element of a screening or diagnostic scale of suicidal ideation and behavior, the lower as and concurrent correlations, and lack of internal structural (EFA, CFA) evidence are concerning, and much more psychometric information is needed to better understand and use the C-SSR.</p> <hd id="AN0127116368-8">Implications for Counseling Practitioners and Researchers</hd> <p>The ability to confidently use assessments that identify suicidal ideation when working with clients is paramount for counselors. Some estimates indicate that approximately one in four mental health professionals will experience a client suicide (Granello & Granello, 2007). Accurate identification is an essential step in the prevention and effective management of suicide ideation. Although no instrument can be 100% conclusive, it can be invaluable for practitioners to have viable instruments they can credibly incorporate in clinical assessment. This is the bottom line: Standardized assessments should be used in conjunction with a clinical interview, pneumonics (e.g., IS PATH WARM, SLAP, NO HOPE), and assessment of risk factors to provide a comprehensive assessment of client lethality (Erford, 2018).</p> <p>Meta-analysis has gained popularity in recent years as a valuable method to synthesize research into a single, more comprehensible product. This meta-analysis reviewed studies of four commonly used suicide ideation assessments to inform the selection of suicide instruments based on criteria deemed important by the clinician. Factors such as administration time, level of administrator training, population match, and psychometric strength can be useful in determining selection.</p> <p>For example, the BSS (Beck & Steer, 1991) can be completed in 5 to 10 minutes, but its administration requires a trained clinician. Two of the total seven studies included in the meta-analysis using the BSS reported high internal consistency, but we could not identify any studies reporting test-retest data. There was strong evidence of concurrent validity. Internal structural and diagnostic validity were reported, but by only a single study. Despite lack of reported statistics for nonclinical samples, the full version of the BSS should provide clinicians with accuracy in identifying suicide ideation in adolescents and adults, although this finding warrants some caution due to the low number of studies identified.</p> <p>The SPS (Cull & Gill, 1992) is similarly quick to administer and score, although a highly trained clinician is required for its administration to adolescents and adults. Our analysis of 38 articles identified strong internal consistency across 10 studies, and test-retest stability in two studies. Strong evidence of concurrent validity was also reported, as well as promising results pertaining to diagnostic validity. However, studies reporting data fit for the four-factor model were inconclusive. The brief version of the SPS, the Suicide Ideation subscale, was also evaluated across eight articles, with comparable psychometric strength, although we were unable to identify any studies reporting data on diagnostic validity.</p> <p>The SIQ (Reynolds, 1988) and SIQ-JR are intended for specific use with adolescents, and we were able to identify 35 articles for this meta-analysis. Very high internal consistency across 14 studies was reported for the SIQ, although test-retest reliability was reported in only a single study. Although the SIQ displayed robust concurrent validity, similar to the BSS, we identified only one internal structural validity study. Although the SIQ-JR resulted in mostly similar psychometric data, the reported accuracy rate for this instrument was very low for use with a clinical population.</p> <p>The C-SSR (Columbia University, 2014) is intended to be a more comprehensive suicide assessment for both adolescents and adults, but we were able to identify only three usable articles to include in this meta-analysis. It is a structured clinical interview in comparison to the other three self-report instruments. Internal consistency for the C-SSR was adequate, but lower than the other three instruments reviewed in this study. Test-retest reliability and concurrent validity were also reported, but we could not identify any evidence for internal structural validity. It should be noted, however, that the C-SSR had near-perfect sensitivity and specificity, meeting or surpassing the other three instruments reviewed.</p> <p>Although counselor education programs using council for accreditation of counseling and related educational programs (CACREP) accreditation standards focus on clinical interviewing and suicide assessment procedures, counselors in training and clinical practice could benefit from instruction and training in the use of standardized assessments of suicide ideation and behaviors. Only the BSS is currently commonly taught in counselor education programs (Neukrug et al., 2013) and commonly used in clinical practice (Peterson et al., 2014), although it was used in outcome studies less frequently than all other instruments except for the relative newcomer, the C-SSR (Columbia University, 2014). The C- SSR is probably the most commonly used suicide ideation screening instrument in suicide and depression research because of lethality safeguards required by the National Institute of Mental Health when conducting federally funded research with this population. Unfortunately, researchers use the C-SSR without reporting on its psychometric properties with the samples studied.</p> <p>Each of the reviewed standardized instruments is easy to administer, score, and interpret, and each has strengths and weaknesses to consider along with use. Table 2 presents an aggregated summary of these strengths and weaknesses. A weakness common to all of the instruments reviewed is a lack of validity or response style scales clinicians could use to help determine whether a client is attempting to create a positive impression (i.e., make the clinician believe the client does not display suicidal ideation and tendencies when indeed the client does), or a negative impression (i.e., make the clinician believe the client does display suicidal ideation and tendencies when indeed the client does not) that could invalidate results.</p> <p>So what are the best choices for use by professional counselors? The C-SSR is an excellent instrument to incorporate into a clinical interview to provide a more structured approach and its outstanding diagnostic validity results will help bolster the accuracy of decisions. When considering use of self-report instruments to supplement the clinical interview and triangulate with conclusions of the pneumonics and risk factors, the BSS is the best choice for use with adults and the SIQ (and SIQ-JR) is the best choice for use with adolescents. Even though the SPS was the most frequently cited suicide ideation instrument in the extant literature, the poor showing in diagnostic validity studies counterindicates confidence in usefulness. Thus, counselor educators are encouraged to incorporate the C-SSR, BSS, and SIQ into course instruction and training of professional counselors. Until professional counselors are exposed to and instructed in use of these and other standardized instruments, decision accuracy will suffer and the standard of care expected of the American Counseling Association (ACA) Code of Ethics (ACA, 2014) might come up short. Triangulation of structured clinical interview, self-report, pneumonics, and risk factor assessments related to suicide ideation and behaviors should lead to robust, consistent, and accurate clinical decisions.</p> <p>As this meta-analysis has indicated, there is a need for more studies with these instruments using larger and more diverse samples. Although these four instruments might provide clinicians with tools to initiate conversations about suicide and provide a structure to the overall evaluation process, their clinical utility may be limited. Because suicide rates are indicated to be higher with marginalized populations, it is important that the utility and generalizability of these suicide ideation instruments are studied with these populations. Randomized assignment of clients and pretest-posttest design methodology could be useful. Cumulative evidence of the efficacy of these instruments is warranted, and clinicians should not substitute clinical judgment and evaluation for suicide screening based on these measures alone.</p> <p>There is a call for evidence-based practice in the counseling field to inform assessment and treatment practices. Meta-analysis has been identified as one of the most legitimate methods of summarizing findings of empirically based research (Rosenthal et al., 2006). As such, researchers using assessment instruments in clinical studies should consistently report reliability and validity data to facilitate psychometric comparisons among different measures. As counselors become better consumers of research and conduct quality studies, evidence for the selection of instrumentation for both practice and research will improve.</p> <hd id="AN0127116368-9">Study Limitations</hd> <p>A systematic set of criteria were followed in the selection of articles for this meta-analysis. Extensive electronic and hand searches of published literature were undertaken with the qualifiers that each study reviewed must be in English and have some type of reliability or validity data. The results were then pooled and analyzed quantitatively to further evaluate, compare, and contrast the four most commonly used suicide ideation instruments.</p> <p>Rosenthal, Hoyt, Ferrin, Miller, and Cohen(2006)pointed out that although using published literature is a common methodological procedure, it does lend itself to three potential biases that are a limitation of the findings. These include publication, search, and selection biases. Because sometimes only those studies with positive results are published, there is the possibility that publication bias has occurred. Because studies with no significant results or even negative results might not have been chosen for publication in a peer-reviewed journal, which was a criterion for inclusion in this meta-analysis, it was impossible to include the results of those studies that in turn might have altered the analysis results. Additionally, only articles that had been published in English were included, which means there could have been other-language studies with potential impact not included. Not all journals have the same rigor for consideration, so quality among the articles included might also vary.</p> <p>There is the potential that search bias might have occurred in the selection process. Even though strict criteria and procedures for inclusion were followed, relevant studies might have been omitted. The key search words used included the instrument name and acronym -- however, there is a possibility that pertinent articles were excluded.</p> <p>Selection bias is another potential limitation. The initial identification phase in the meta-analysis process can produce long lists of potential studies for inclusion. On further analysis, many of these studies might not be relevant. Discrepancies might have occurred also if studies of lower quality met the selection criteria.</p> <p>The most important limitation for this study was lack of psychometric data for some of the suicide instruments included in this meta-analysis. Although the BSS generated the most candidate articles (<reflink idref="bib420" id="ref9">420</reflink>) from 1993 to 2013, only seven articles met the selection criteria for English language and reported validity and reliability data, significantly limiting the available studies with published psychometric data that we could analyze. Similarly, searches for the SPS resulted in 188 candidate articles, but only 38 were fit for inclusion. The C-SSR followed suit, with 148 candidate articles, leading to only three selected articles. Finally, searches for the SIQ produced the lowest number of candidate articles, at 125, but yielded 35 included articles. Even those studies that fit the inclusion criteria did not consistently assess reliability and validity for their chosen instruments, further limiting confidence for the recommendation of one instrument over the other. Researchers are urged to report study reliability and validity data to help bolster our collective understanding of how these instruments can be most effectively used in research and clinical practice.</p> <p> <bold> CONTACT </bold> Bradley T. Erford @ bradley.t.erford@vanderbilt.edu Peabody College at Vanderbilt University, Human and Organizational Development,230 Appleton Place, Nashville,TN 37203-5721, USA.</p> <hd id="AN0127116368-10">Table 1. Concurrent Validity Studies Using the Beck Scale for Suicide Ideation (BSS), Suicide Ideation Questionnaire (SIQ), Suicide Probability Scale (SPS), and Columbia-Suicide Severity Rating Scale (C-SSR)</hd> <p> <ephtml> <div class="table-size-normal table-border"><table border="1"> <tr> <td>Convergent Comparison</td> <td>j</td> <td>n</td> <td>r [95% CI]</td> <td>Studies</td> </tr> <tr> <td>BSS with</td> <td></td> <td></td> <td></td> <td></td> </tr> <tr> <td>C-SSR</td> <td>2</td> <td>683</td> <td>.58 [.51, .65]</td> <td>Posner et al. (2011)</td> </tr> <tr> <td>SPS</td> <td>1</td> <td>67</td> <td>.65 [.41, .89]</td> <td>Bisconer & Gross (2007)</td> </tr> <tr> <td>Adult Suicide Ideations Questionnaire (ASIQ)</td> <td>1</td> <td>67</td> <td>.64 [.40, .88]</td> <td>Bisconer & Gross (2007)</td> </tr> <tr> <td>Suicide Assessment Scale Self-Report (SUAS-S)</td> <td>1</td> <td>52</td> <td>.66 [.39, .93]</td> <td>Koldsland et al. (2007)</td> </tr> <tr> <td>Beck Depression Inventory (BDI)</td> <td>4</td> <td>535</td> <td>.58 [.50, .66]</td> <td>Bisconer & Gross (2007); Bowen et al. (2011); Cochrane-Brink et al. (2000); Hirsch (2004)</td> </tr> <tr> <td>Mood Disorder Questionnaire (MDQ)</td> <td>1</td> <td>129</td> <td>.19 [.02, .36]</td> <td>Bowen et al. (2011)</td> </tr> <tr> <td>Modified SAD PERSONS Scale (MSPS)</td> <td>1</td> <td>55</td> <td>.75 [.49,1.00]</td> <td>Cochrane-Brink et al. (2000)</td> </tr> <tr> <td>Beck Hopelessness Scale (BHS)</td> <td>3</td> <td>406</td> <td>.55 [.45, .65]</td> <td>Bisconer & Gross (2007); Cochrane-Brink et al. (2000); Hirsch (2004)</td> </tr> <tr> <td>Beck Anxiety Inventory (BAI)</td> <td>2</td> <td>122</td> <td>.55 [.37, .73]</td> <td>Bisconer & Gross (2007); Cochrane-Brink et al. (2000)</td> </tr> <tr> <td>Affective Lability Scale (ALS)</td> <td>1</td> <td>129</td> <td>.38 [.21, .38]</td> <td>Bowen et al. (2011)</td> </tr> <tr> <td>Perceived Stress Scale (PSS)</td> <td>1</td> <td>129</td> <td>.41 [.24, .58]</td> <td>Bowen et al. (2011)</td> </tr> <tr> <td>Eysenck Neuroticism Scale (N-ERQ)</td> <td>1</td> <td>129</td> <td>.29 [.12, .46]</td> <td>Bowen et al. (2011)</td> </tr> <tr> <td>SIQ with</td> </tr> <tr> <td>Suicide Opinion Questionnaire (SOQ)</td> <td>1</td> <td>81</td> <td>.70 [.48, .92]</td> <td>Lester (2004)</td> </tr> <tr> <td>Suicide Resiliency Inventory (SRI-25)</td> <td>1</td> <td>239</td> <td>-.67 [-.54, -.80]</td> <td>Rutteretal.(2008)</td> </tr> <tr> <td>Reasons for Living Inventory (RFL)</td> <td>1</td> <td>320</td> <td>-.66 [-.55, -.77]</td> <td>Kumar et al. (2008)</td> </tr> <tr> <td>Suicide Intent Scale (SIS)</td> <td>1</td> <td>151</td> <td>.26 [.10, .42]</td> <td>Spirito et al. (1996)</td> </tr> <tr> <td>BDI</td> <td>3</td> <td>1,030</td> <td>.58 [.52, .64]</td> <td>Chang (2002); Reynolds (1991); Weber et al. (1997)</td> </tr> <tr> <td>Reynolds Adolescent Depression Scale (RADS)</td> <td>1</td> <td>151</td> <td>.47 [.31, .63]</td> <td>Spirito et al. (1996)</td> </tr> <tr> <td>Minnesota Multiphasic Personality Inventory Depression subscale</td> <td>1</td> <td>118</td> <td>.64 [.46, .82]</td> <td>Osman et al. (1999)</td> </tr> <tr> <td>BHS</td> <td>4</td> <td>1,485</td> <td>.50 [.45, .55]</td> <td>Gencoz et al. (2007); Lynch et al. (2004); Reynolds (1991); Weber et al. (1997)</td> </tr> <tr> <td>Hopelessness Scale for Children (HSC)</td> <td>1</td> <td>151</td> <td>.49 [.33, .65]</td> <td>Spirito et al. (1996)</td> </tr> <tr> <td>UCLA Loneliness Scale</td> <td>1</td> <td>185</td> <td>.52 [.38, .66]</td> <td>Weber et al. (1997)</td> </tr> <tr> <td>SIQ-Junior High version (SIQ-JR) with Reynolds Suicidal Behaviors Interview (SBI)</td> <td>5</td> <td>690</td> <td>.66 [.59, .73]</td> <td>Bergen (1999); King et al. (1993); Prinstein et al. (2000); Reynolds (1990); Reynolds & Mazza (1999)</td> </tr> <tr> <td>SPS with</td> </tr> <tr> <td>RFL</td> <td>5</td> <td>1,543</td> <td>-.54 [-.49, -.59]</td> <td>Eryilmaz (2012); Gutierrez et al. (2002); Kopper et al. (2001); Osman et al. (2000); Osman & Kopper (1998)</td> </tr> <tr> <td>Center for Epidemiological Studies-Depression</td> <td>2</td> <td>313</td> <td>.64 [.53, .75]</td> <td>Morrison & O'Connor (2008); O'Connor & Noyce (2008)</td> </tr> <tr> <td>BHS</td> <td>5</td> <td>511</td> <td>.56 [.47, .65]</td> <td>Bisconor & Gross (2007); D'Zurilla & Chang (1998); Kopper et al. (2001); Lee (1992); Morrison & O'Connor (2008)</td> </tr> <tr> <td>BSS</td> <td>2</td> <td>112</td> <td>.51 [.32, .70]</td> <td>Bisconor & Gross (2007); Lee (1992)</td> </tr> <tr> <td>BDI</td> <td>4</td> <td>858</td> <td>.67 [.60, .74]</td> <td>Bisconor & Gross (2007); Borthick (1998); Demirbas et al. (2003); D'Zurilla & Chang (1998)</td> </tr> <tr> <td>Positive Affect Negative Affect Schedule (PANAS+)</td> <td>1</td> <td>475</td> <td>.62 [53, .71]</td> <td>Gutierrez et al. (2002)</td> </tr> <tr> <td>Positive Affect Negative Affect Schedule (PANAS-)</td> <td>1</td> <td>475</td> <td>.53 [.46, .62]</td> <td>Gutierrez et al. (2002)</td> </tr> <tr> <td>MMPI Depression subscale</td> <td>1</td> <td>475</td> <td>.68 [.59, .77]</td> <td>Gutierrez et al. (2002)</td> </tr> <tr> <td>Response Style Questionnaire-Short Form</td> <td>1</td> <td>81</td> <td>.72 [50, .92]</td> <td>Morrison & O'Connor (2008)</td> </tr> <tr> <td>BAI</td> <td>1</td> <td>67</td> <td>56 [.32, .80]</td> <td>Bisconor & Gross (2007)</td> </tr> <tr> <td>SIQ</td> <td>1</td> <td>67</td> <td>.80 [56,1.00]</td> <td>Bisconor & Gross (2007)</td> </tr> <tr> <td>Firestone Assessment of Self-Destructive Thoughts</td> <td>1</td> <td>1,358</td> <td>.76 [.71, .81]</td> <td>Firestone & Firestone (1998)</td> </tr> <tr> <td>C-SSR with</td> </tr> <tr> <td>BSS</td> <td>2</td> <td>683</td> <td>58 [.51, .65]</td> <td>Posner et al. (2011)</td> </tr> <tr> <td>Beck Lethality Scale</td> <td>1</td> <td>234</td> <td>.79 [.66, .92]</td> <td>Posner et al. (2011)</td> </tr> <tr> <td>Montgomery-Asberg Depression Rating Scale</td> <td>1</td> <td>472</td> <td>.63 [.54, .72]</td> <td>Posner et al. (2011)</td> </tr> <tr> <td>SIQ-JR</td> <td>1</td> <td>234</td> <td>.36 [.23, .49]</td> <td>Posner et al. (2011)</td> </tr> </table></div> </ephtml> </p> <p>Note. j = number of articles in which the instrument was used asan outcome measure.</p> <hd id="AN0127116368-11">Table 2. Characteristics and Meta-Analysis Psychometric Summary of the Beck Scale for Suicide Ideation (BSS), Suicide Ideation Questionnaire (SIQ), Suicide Probability Scale (SPS), and Columbia-Suicide Severity Rating Scale (C-SSR)</hd> <p> <ephtml> <div class="table-size-normal table-border"><table border="1"> <tr> <td></td> <td></td> <td></td> <td></td> <td></td> <td>Reliability</td> </tr> <tr> <td>Scale</td> <td>Age</td> <td>Items</td> <td>Time</td> <td>Response</td> <td>J</td> <td>n</td> <td>α</td> <td>r<sub>tt</sub>(T)</td> </tr> <tr> <td>BSS</td> <td>Adult</td> <td>21</td> <td>5-10</td> <td>Self-report</td> <td>7</td> <td>1,059</td> <td>.91</td> <td>N/A</td> </tr> <tr> <td>SIQ (& SIQ-JR)</td> <td>13+</td> <td>30</td> <td>10</td> <td>Self-report</td> <td>35</td> <td>10,942</td> <td>.95</td> <td>.86 (1 week)</td> </tr> <tr> <td>SPS</td> <td>15+</td> <td>36</td> <td>10</td> <td>Self-report</td> <td>38</td> <td>9,254</td> <td>.91</td> <td>.71 (1-3 months)</td> </tr> <tr> <td>C-SSR</td> <td>15+</td> <td>5</td> <td>25</td> <td>Interview</td> <td>3</td> <td>917</td> <td>.84</td> <td>.90</td> </tr> <tr> <td></td> <td>Validity</td> </tr> <tr> <td>Scale</td> <td>Convergent</td> <td>Internal</td> <td>Diagnostic</td> <td>Interpretation</td> </tr> <tr> <td>BSS</td> <td>Moderate</td> <td>Minimal</td> <td>Strong</td> <td>Criterion (1+)</td> </tr> <tr> <td>SIQ (& SIQ-JR)</td> <td>Strong</td> <td>Minimal</td> <td>Moderate</td> <td>Criterion (41/31)</td> </tr> <tr> <td>SPS</td> <td>Moderate-strong</td> <td>Minimal</td> <td>Poor</td> <td>Normed (78)</td> </tr> <tr> <td>C-SSR</td> <td>Moderate-strong</td> <td>Minimal</td> <td>Excellent</td> <td>Criterion (1+)</td> </tr> </table></div> </ephtml> </p> <ref id="AN0127116368-12"> <title> Notes on Contributors </title> <blist> <bibl id="bib1" type="bt"></bibl> <bibtext>Bradley T. 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  Data: Selecting Suicide Ideation Assessment Instruments: A Meta-Analytic Review
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  Data: Routledge. Available from: Taylor & Francis, Ltd. 530 Walnut Street Suite 850, Philadelphia, PA 19106. Tel: 800-354-1420; Tel: 215-625-8900; Fax: 215-207-0050; Web site: http://www.tandf.co.uk/journals
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  Data: Psychometric meta-analyses and reviews were provided for four commonly used suicidal ideation instruments: the Beck Scale for Suicide Ideation, the Suicide Ideation Questionnaire, the Suicide Probability Scale, and Columbia--Suicide Severity Rating Scale. Practical and technical issues and best use recommendations for screening and outcome research are offered.
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