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195 The Journal of Social Psychology, 2009, 149(2), 195–211 Copyright © 2009 Heldref Publications Why Not Procrastinate? Development and Validation of a New Active Procrastination Scale JIN NAM CHOI Seoul National University SARAH V. MORAN McGill University ABSTRACT. Procrastination has been studied as a dysfunctional, self-effacing behavior that ultimately results in undesirable outcomes. However, A. H. C. Chu and J. N. Choi (2005) found a different form of procrastination (i.e., active procrastination) that leads to desirable outcomes. The construct of active procrastination has a high potential to expand the time management literature and is likely to be adopted by researchers in multiple areas of psychology. To facilitate the research on this new construct and its further integration into the literature, the authors developed and validated a new, expanded measure of active procrastination that reliably assesses its four dimensions. Using this new measure of active procrastination, they further examined its nomological network. The new 16-item measure is a critical step toward further empirical investigation of active procrastination. Keywords: active procrastination, construct validation, personality, scale development, time management “It’s easy to see procrastination as a bad thing, something you do when you should be doing something else . . . [but] embracing procrastination . . . can help restore your motivation.” (B. Halford, 2006) MOST RESEARCHERS (e.g., Bond & Feather, 1988; Ellis & Knaus, 1977; Ferrari, 2001; Knaus, 2000; Tice & Baumeister, 1997) have defined procrastina- tion along pessimistic behavioral lines with relatively negative consequences. For example, Harriott and Ferrari (1996) found procrastination to be a prevalent behavior among students and adults, hampering their ability to successfully complete tasks on time. Recently, Chu and Choi (2005) provided an alternative Address correspondence to Jin Nam Choi, College of Business Administration, Seoul National University, Shinlim-dong, San 56-1, Kwanak-ku, Seoul 151-916, South Korea; jnchoi@snu.kr (e-mail). 196 The Journal of Social Psychology perspective and demonstrated that not all procrastination behaviors are harm- ful or are precursors of negative consequences. Specifically, they proposed two distinct types of procrastinators. Passive procrastinators are traditional procras- tinators who postpone their tasks until the last minute because of an inability to make the decision to act in a timely manner. In contrast, active procrastinators make intentional decisions to procrastinate, using their strong motivation under time pressure, and they are able to complete tasks before deadlines and achieve satisfactory outcomes. Contrary to popular wisdom, Chu and Choi (2005) found that active procras- tinators did possess desirable behavioral and attitudinal characteristics, leading to positive personal outcomes. Their results were particularly provocative because although active procrastinators reported the same level of procrastination as did their traditional or passive counterparts, they demonstrated time perceptions, atti- tudes, coping styles, and academic performance that were nearly identical to (and in some cases even better than) those of nonprocrastinators. By differentiating the two types of procrastinators, Chu and Choi moved toward a more sophisticated understanding of procrastination as a task-related behavior. In their initial conceptualization, Chu and Choi (2005) proposed that active procrastination is characterized by the following four characteristics: (a) prefer- ence for time pressure, (b) intentional decision to procrastinate, (c) ability to meet deadlines, and (d) satisfaction with outcome. Developing a 12-item scale, they successfully revealed the presence of a new, constructive form of procrastination that was, in many respects, quite different than the traditional form of procrastina- tion. Given the intuitive appeal and the novel nature of the active procrastination construct, we believe that researchers in various areas, including social, personal- ity, educational, and industrial and organizational psychology, will be motivated to reexamine the role of procrastination in their theoretical spaces. Not surprisingly, scholars in various disciplines, including marketing, engi- neering, social psychology, and personality psychology, have promptly recognized the rather counterintuitive assertions and findings related to active versus passive procrastination (e.g., Bernold, 2007; Hu, Huhmann, & Hyman, 2007). In his lengthy discussion of implications of active procrastination, Bui (2007) stated that Chu and Choi (2005) “introduced a novel idea for the area of procrastination research: the notion that delaying one’s work can actually be helpful and related to positive characteristics. Researchers have studied that idea very little, and it is worthy of further investigation” (p. 207). Despite Bui’s call for additional empirical studies on active procrastination, in the current literature, researchers now simply acknowledge the presence of an adaptive type of procrastinator in interpreting their findings (e.g., Alexander & Onwuegbuzie, 2007; Howell & Watson, 2007), perhaps because of the nascent developmental stage of this construct and lack of empirical research using active procrastination as a measured variable. Unfortunately, Chu and Choi (2005) failed to confirm the hypothesized four- dimensional structure of active procrastination and to provide a valid and reliable Choi & Moran 197 measurement tool for further investigation of the construct. Moreover, the reli- ability of Chu and Choi’s scale was only marginal (α = .67), which presents the need for further refinement of the scale. In the present study, building on Chu and Choi’s initial conceptualization, we elaborate on the theoretical underpin- nings of the four defining characteristics of active procrastination. On the basis of this theoretical development, we constructed and empirically validated a new measure of active procrastination by using the widely accepted scale validation procedure (Hinkin, 1998). We further expanded the nomological network of active procrastination by examining its relations with other general personal- ity characteristics. By providing an instrument that can yield reliable and valid responses of active procrastination, this study paves the way for more rigorous empirical investigation of this novel construct and facilitates its integration into the literature. Four Defining Characteristics of Active Procrastination As a multidimensional construct, active procrastination is an observable behavioral characteristic that encompasses a person’s affective preference for time pressure, cognitive decision to procrastinate, behavioral capacity to meet deadlines, and ability to achieve satisfactory outcomes. Chu and Choi (2005) mentioned that they used these four dimensions of active procrastination to construct measurement items, but they did not provide any theoretical reasons why these four dimensions comprise critical defining characteristics of active procrastination. However, to better understand the construct of active procrastination, we must specify the aspects of human behavior that underlie its defining characteristics, including behaviors related to time management, goal achievement, and performance. The benefit of active procrastination may be related to an individual’s capacity to flexibly organize time and the ability to self-motivate, coupled with constructive use of time pressures that effectively drive active procrastinators toward their goals (Golwitzer & Bayer, 1999). These processes signify effective and efficient self-regulatory mechanisms that create a movement toward objectives and their successful attainment. Next, we elaborate further on the four dimensions of active procrastination. Preference for pressure.Although it has been argued that procrastination leads to time pressure that causes stress, for some people, time pressure can create a feel- ing of challenge that does not necessarily engender negative psychological states (Freedman & Edwards, 1988). When confronted with last-minute time pressure, active procrastinators tend to enjoy the feeling of being challenged, which results in increased motivation (Chu & Choi, 2005). Active procrastinators seem to prefer pressure and thus are motivated by both an intrinsic need to deal with challenge and external demands to complete the task on time (Deci & Ryan, 1985). 198 The Journal of Social Psychology Intentional decision to procrastinate. Traditional, or passive, procrastinators tend to drift from one activity to another without much planning or organiza- tion of their time (Bond & Feather, 1988). In contrast, nonprocrastinators have been viewed as those who are good at managing their time in an orderly and efficient manner (Ellis & Knaus, 1977; Knaus, 2000). In contrast with both pas- sive procrastinators and nonprocrastinators, active procrastinators preplan their task activities in an organized way though they do not develop or adhere to a rigid schedule or time structure. With this elasticity in time perception and use patterns, active procrastinators are willing to make deliberate decisions to post- pone things they have planned to do, and they will change their schedule even on short notice. Thus, instead of being fixated on their routine or prescheduled activities (characteristic of nonprocrastinators), active procrastinators freely and intentionally reshuffle their task activities to respond to changing external demands (Chu & Choi, 2005). Ability to meet deadlines. The main reason that procrastination has been regarded as a self-handicapping behavior is that procrastinators often fail to complete tasks on time, thus producing disappointing results for themselves (Ferrari, 2001; Knaus, 2000). This pattern is perhaps due to passive procrastinators’ tendency to underestimate the time needed to complete a particular task and thus to be overwhelmed or overstressed by time pressure at the last minute (Tice & Bau- meister, 1997). Active procrastinators, in contrast, are able to properly estimate the minimum amount of time required to finish a task and push themselves to proceed efficiently toward the goal, even with (or perhaps because of) last minute pressure. This difference may be due to distinct ways of dealing with stressful situations: Unlike passive procrastinators, who largely rely on emotional- or avoidance-coping strategies, active procrastinators use more task-oriented coping strategies under stress (Chu & Choi, 2005). Outcome satisfaction. Because active procrastinators know how to motivate them- selves under pressing conditions, make intentional decisions to procrastinate, and complete tasks on time, they usually obtain satisfactory task outcomes even though they procrastinate. At the core of passive procrastination is the failure to control one’s focus on the task at hand and the tendency to gravitate toward activi- ties that are more pleasant than carrying out the task (Tice & Baumeister, 1997). Passive procrastinators desire immediate gratification of their needs, which can alleviate stress in the short run but can result in self-defeating outcomes (Harriott & Ferrari, 1996; Knaus, 2000). In this situation, the discrepancy between what a person should do and what he or she actually does leads to a negative outcome. In contrast, active procrastinators intentionally decide to put off their tasks, but at the last moment, through the effective and efficient use of their time, they suc- cessfully complete the task, achieving a rewarding outcome. Choi & Moran 199 Nomological Network Associated With Active Procrastination Once the difference between traditional and active procrastination is estab- lished, it is imperative to construct a nomological network of theoretically related variables. According to Cronbach and Meehl (1955), demonstrating a construct’s relations with other relevant constructs will clarify what the con- struct is and increase its distinctiveness in a theoretical space. This provision of observable interpretations of the construct in relation to other relevant constructs is a critical component of construct validation (Chen, Mathieu, & Bliese, 2004; Hinkin, 1998). Chu and Choi (2005) showed that active procrastination is positively related to purposive use of time and perceived time control, whereas it is negatively asso- ciated with time structure. Because active procrastinators prefer time pressure and frequently postpone or reprioritize task activities, they are likely to be more sensitive about the goals of their time use and have less rigid conceptions of time, which, in turn, provides them with an increased sense of control over their time. Similarly, Macan (1994) found that individuals who made to-do lists and adhered to scheduled activities (highly structured time) perceived less control over their time. In the present study, we proposed that active procrastination is positively related to polychronicity, or preference to work on several tasks simultaneously (Bluedorn, Kalliath, Strube, & Martin 1999; Hecht & Allen, 2005). Because of their fluid perception of time, high sense of time control, and willingness to change their work schedule, active procrastinators may have a polychronic, instead of monochronic, orientation to time, engaging in and managing multiple tasks at the same time. Although procrastination has mostly been studied in terms of its negative outcomes (Ellis & Knaus, 1977; Ferrari, 2001), Chu and Choi (2005) showed that active procrastination has positive implications for individuals in terms of self-efficacy, depression, stress coping, and performance. Successful time man- agement and self-regulation need not necessarily mean rigid regulation of activi- ties (Macan, Shahani, Dipboye, & Phillips, 1990). By freeing themselves from a strict time structure and shifting attention from routine and schedules to effective accomplishment of the goal, active procrastinators may experience less stress and engage in more constructive responses to work-related stress (e.g., time pressure), which, in turn, induces higher performance and greater overall life satisfaction. In the present study, we further enriched the nomological network of active procrastination by examining its relations to other personality characteristics. To this end, we used the Big Five personality framework, which has been widely accepted as representing relatively independent and comprehensive dimensions of personality (McCrae & Costa, 1985). These dimensions have also been found to have implications for individual performance (Barrick & Mount, 1991). The five personality dimensions are characterized by discrete qualities: (a) conscientiousness is associated with being exacting, disciplined, planning, and 200 The Journal of Social Psychology responsible; (b) emotional stability is characterized by calmness, composure, and a serene attitude; (c) extroversion is associated with being sociable, assertive, and active; (d) agreeableness represents personal qualities such as cooperation, sympathy, and courtesy; and (e) openness to experience is associated with being intelligent, imaginative, and broad-minded. We expected active procrastination to be negatively related to conscientiousness because a conscientious person is well-organized and disciplined; therefore, he or she is more likely to be a non- procrastinator than an active procrastinator. We further predicted that active pro- crastination is positively related to emotional stability and extraversion because active procrastinators need high levels of self-confidence and positive energy, which allow them to choose to actively reorganize their task activities and which inoculate themfrom stress caused by time pressure at the last moment. Method Participants and Data Collection Procedure We invited undergraduate business students from a Canadian university to participate in the present study by filling out a questionnaire entitled “Survey of University Students’ Use of Time.” Participation was voluntary, with a raffle of seven $50 U.S. prizes as an incentive. Of the 300 questionnaires distributed, 185 questionnaires were returned (a response rate of 61.7%). This sample was 63% female (n = 115) and 37% male (n = 68). Most participants (96.8%) were full- time students with an average university attendance of 2.8 years. The distribu- tion of the participants’ ethnic backgrounds was as follows: 74.1% White, 1.6% African American, 2.7% Hispanic, and 20% Asian. More than half of the sample (59.4%) spoke English as their first language, followed by French (22.7%) and other languages (17.3%). Measures In addition to the new measure of active procrastination, the survey included various time-related perceptions and behaviors, personality variables, and individual outcomes. All constructs were measured using multiitem indexes with a response for- mat of a 7-point Likert-type scale ranging from 1 (not at all true) to 7 (very true). Active procrastination. Drawing on the 12-item measure developed by Chu and Choi (2005), we constructed a new, expanded scale of active procrastination com- prising 40 items. We developed these items by taking into account various cogni- tive, affective, and behavioral mechanisms that may underlie the four dimensions of active procrastination (i.e., preference for time pressure, intentional decision to procrastinate, ability to meet deadlines, and outcome satisfaction). Each dimen- Choi & Moran 201 sion was assessed by 10 items. We checked the face validity and content coverage of the 40 items by pilot-testing the questionnaire and obtaining feedback from 10 undergraduate students. The 40-item scale was subsequently slightly modified before administration to the study sample (a full set of items are available from Jin Nam Choi upon request). Passive procrastination. The level of passive or traditional procrastination was mea- sured by five items (α = .74; e.g., “Even after I make a decision I delay acting upon it”) that have been used in previous studies (Mann, 1982; Schouwneburg, 1995). Time use and perceptions. We assessed participants’ structured use of time (time structure) using four items (α = .70; e.g., “I feel uneasy if I have to skip things that I am used to doing every day”) developed by Bond and Feather (1988). The extent to which participants used their time with clear goals (purposive use of time) was measured by Bond and Feather’s three-item scale (α = .70; e.g., “I tend to wander rather aimlessly from one activity to another during the day,” reverse coded). We measured perceived time control using three items (α = .81; e.g., “I can use my time the way I want to use it”) developed by Macan et al. (1990). To measure the extent to which participants preferred to engage in multiple tasks simultaneously (polychronicity), we adopted four items (α = .81; e.g., “I like to juggle several activities at the same time”) developed by Bluedorn et al. (1999). Big Five personality characteristics. To measure participants’ personality attri- butes, we used Goldberg’s (1992) markers for the Big Five personality factors. The scale consisted of several adjectives pertaining to each personality attribute. For example, conscientiousness was measured by the degree to which participants rated themselves as organized, efficient, careful, and conscientious (four-item scale, α = .76). The emotional stability scale measured the extent to which par- ticipants saw themselves as anxious, emotional, irritable, and nervous (four items, α = .72). Extraversion was measured by the following four adjectives (α = .71): extraverted, assertive, energetic, and active. The agreeableness scale included five descriptors (α = .83): agreeable, kind, cooperative, sympathetic, and warm. Last, the openness to experience scale comprised five descriptors (α = .79): intel- lectual, creative, imaginative, bright, and innovative. Individual outcomes. The present study included three individual outcomes. First, life satisfaction was measured by a four-item index (α = .82; e.g., “In general, I am satisfied with my life”). Second, as a measure of academic per- formance, participants reported their GPA. Last, participants self-rated their performance level in the class (six categories ranging from below average to top 10% of the class). 202 The Journal of Social Psychology Results Scale validity refers to the relation between a theoretical construct and its operationalization or measure (Cronbach & Meehl, 1955). Therefore, the aim of scale validation is to “test the extent to which operationalizations of a construct ‘behave’ in a manner consistent with the theoretical expectations” (Chen et al., 2004, p. 277). We validated our new measure of active procrastination accord- ing to the common practice of scale development (Gerbing & Anderson, 1988; Hinkin, 1998). Before we analyzed the data, we checked the distribution of responses to scales used by examining skewness and kurtosis. This examination revealed that all variables were normally distributed, with the exception of agreeableness and life satisfaction. In addition, gender, age, race, and school year showed no significant association with any dimension or with the composite score of active procrastination. Exploratory Factor Analysis (EFA) With a multidimensional construct, the first criterion to consider is the underlying factor structure of the scale items. To this end, we conducted an EFA of the 40 items developed to measure the four dimensions of active procrastina- tion, followed by a confirmatory factor analysis (CFA). We carried out a series of EFAs to obtain a preliminary view of the overall relational structure of the items, as well as to eliminate items that were obvious outliers (i.e., no connections with other items in the same dimension) or conceptually ambiguous (i.e., representing multiple dimensions). The first EFA with all 40 items using principal component analysis with varimax rotation generated 10 factors with eigenvalues ranging from 1 to 6. One by one, we removed items that constituted a single-item factor or had high cross- loadings on multiple factors. While doing so, we also considered the content domain represented by each item so that the final EFA solution offered a balanced representation of the four dimensions underlying active procrastination. After we removed 24 items, the EFA resulted in a 16-item, 4-factor solution that explained 61% of the total item variance. As shown in Table 1, each factor included four items representing specific dimensions of active procrastination. In this final EFA model, each factor showed eigenvalues between 2.1 and 2.8 and accounted for 13–17% of the total variance, indicating that each dimension makes a fairly comparable, balanced contribution to the entire construct. CFA We tested the underlying factor structure of the 16 items obtained from the EFA by imposing the theoretical expectations through the CFA. To validate the hypothesized multidimensional structure, we created a two-layer factor model in Choi & Moran 203 T A B L E 1 . L is t of I te m s an d F ac to r L oa di ng s fo r th e N ew S ca le o f A ct iv e P ro cr as ti na ti on Fa ct or lo ad in g Fa ct or It em 1 2 3 4 1. O ut co m e M y pe rf or m an ce te nd s to s uf fe r w he n I ha ve to r ac e ag ai ns t d ea dl in es ( R ). .7 78 .3 34 .1 16 –. 03 2 sa tis fa ct io n I do n’ t d o w el l i f I ha ve to r us h th ro ug h a ta sk ( R ). .7 63 .2 51 .1 11 .0 38If I p ut th in gs o ff u nt il th e la st m om en t, I’ m n ot s at is fi ed w ith th ei r ou tc om es ( R ). .7 53 .1 88 .1 54 –. 03 9 I ac hi ev e be tte r re su lts if I c om pl et e a ta sk a t a s lo w er p ac e, w el l a he ad o f a de ad lin e (R ). .7 24 .2 26 .2 39 –. 06 4 2. P re fe re nc e fo r It ’s r ea lly a p ai n fo r m e to w or k un de r up co m in g de ad lin es ( R ). .2 30 .8 16 .0 90 .2 27 pr es su re I’ m u ps et a nd r el uc ta nt to a ct w he n I’ m f or ce d to w or k un de r pr es su re ( R ). .1 69 .7 88 .0 73 .0 74 I fe el te ns e an d ca nn ot c on ce nt ra te w he n th er e’ s to o m uc h tim e pr es su re on m e (R ). .3 73 .7 37 .0 60 .0 17 I’ m f ru st ra te d w he n I ha ve to r us h to m ee t d ea dl in es ( R ). .3 60 .6 09 .1 98 .0 39 3. I nt en tio na l To u se m y tim e m or e ef fi ci en tly , I d el ib er at el y po st po ne s om e ta sk s. .1 35 .1 14 .7 85 –. 08 2 de ci si on I in te nt io na lly p ut o ff w or k to m ax im iz e m y m ot iv at io n. –. 04 3 .2 32 .7 02 –. 22 7 In o rd er to m ak e be tte r us e of m y tim e, I in te nt io na lly p ut o ff s om e ta sk s. .2 83 –. 07 0 .6 73 .0 87 I fi ni sh m os t o f m y as si gn m en ts r ig ht b ef or e de ad lin es b ec au se I c ho os e to d o so . .2 11 .1 09 .5 76 –. 00 1 4. A bi lit y to m ee t I of te n st ar t t hi ng s at th e la st m in ut e an d fi nd it d if fi cu lt to c om pl et e th em de ad lin es on ti m e (R ). –. 05 4 .0 52 –. 25 6 .7 38 I of te n fa il to a cc om pl is h go al s th at I s et f or m ys el f (R ). .0 37 .1 55 .0 36 .7 31 I’ m o ft en r un ni ng la te w he n ge tti ng th in gs d on e (R ). –. 03 1 .0 86 –. 36 3 .7 29 I ha ve d if fi cu lty f in is hi ng a ct iv iti es o nc e I st ar t t he m ( R ). –. 02 9 –. 00 4 .2 02 .6 02 N ot e. ( R ) = re ve rs e- co de d ite m . F ac to r lo ad in gs o f th e co rr es po nd in g ite m s w ith in th e su bd im en si on a re in b ol df ac e. 204 The Journal of Social Psychology which the suprafactor of active procrastination was indicated by its four dimen- sions, which were, in turn, indicated by its four corresponding items (Arbuckle, 2005). This two-stage factor model was consistent with the empirical patterns observed in the present data, exhibiting acceptable model fit, χ2(100, N = 185) = 186.24, p < .001; comparative fit index = .92; root mean square error of approxi- mation = .058). Attempts to reduce the number of dimensions from four to three or two resulted in a significantly worse fit (all ps < .01, based on χ2 difference tests). In the four-dimensional model, all four dimensions were significant indica- tors of the suprafactor of active procrastination (all ps < .05), and all items loaded significantly on their corresponding dimensions (all ps < .001), supporting the theoretically predicted factor structure and convergent validity of responses to the new scale of active procrastination (Gerbing & Anderson, 1988). Scale Reliability Following validation of the dimensional structure of the construct, each scale must be checked for internal consistency to ensure that it represents a coherent, reliable assessment of a construct (Chen et al., 2004). Because reli- ability represents the extent to which the scale produces scores that are free from measurement error, it is a necessary (though not sufficient) condition of a sound measure (Hinkin, 1998). As shown in Table 2, the level of reliability (Cronbach’s α) associated with the current participants’ responses to the scales assessing the four dimensions ranged between .70 and .83, providing evidence of acceptable internal consistency. The participants’ responses to the entire 16-item scale of active procrastination also exhibited an acceptable reliability coefficient of .80. Nomological Network With the underlying factor structure validated and acceptable scale reliabili- ties verified, the next step for scale validation is to check predictive or criterion- related validity, which involves an examination of the nomological network of the construct (Chen et al., 2004; Hinkin, 1998). To test whether the active procrasti- nation scale produces the theoretically predicted relations with other established constructs, we examined their correlation coefficients (see Table 2). The active procrastination score was not related to traditional procrastina- tion (r = .07, ns), further confirming that it is a distinct form of procrastination (Chu & Choi, 2005). Also supporting our expectations, active procrastination was negatively related to time structure (r = –.22, p < .01), which indicates that active procrastinators have a fluid, flexible concept of time. In contrast, it was positively associated with time control and polychronicity (r = .26, p < .001 and r = .19, p < .01, respectively), suggesting that active procrastinators tend to engage in more multitasking and perceive greater sense of control over their time than do others. Choi & Moran 205 T A B L E 2 . M ea ns , S ta nd ar d D ev ia ti on s, R el ia bi lit ie s, a nd I nt er sc al e C or re la ti on s V ar ia bl es M SD 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 16 17 18 1 . A ct iv e pr oc ra st in at io n 4. 39 0. 82 .8 0 — 2 . P re fe re nc e fo r pr es su re 4. 35 1. 31 .8 3 .8 2 — 3 . I nt en tio na l d ec is io n 3. 81 1. 28 .6 2 .3 1 .7 0 — 4 . A bi lit y to m ee t de ad lin es 5. 21 1. 02 .3 7 .1 5 –. 11 .7 0 — 5 . O ut co m e sa tis fa ct io n 4. 19 1. 37 .8 1 .6 1 .4 1 –. 05 .8 3 — 6 . P as si ve p ro cr as tin at io n 4. 04 1. 09 .0 7 .0 8 .3 3 –. 61 .2 5 .7 4 — 7 . T im e st ru ct ur e 4. 42 1. 27 – .2 2 –. 26 – .1 2 .1 6 –. 30 – .2 3 .7 0 — 8 . P ur po si ve u se o f tim e 4. 82 1. 26 .1 0 .1 6 –. 23 .3 5 .0 3 –. 34 .0 4 .7 0 — 9 . T im e co nt ro l 4. 73 1. 19 .2 6 .1 9 .0 9 .4 8 –. 01 – .3 8 .2 0 .3 0 .8 1 — 10 . P ol yc hr on ic ity 4. 09 1. 28 .1 9 .1 0 .2 0 .0 1 .1 6 .0 6 .0 4 –. 06 .1 2 .8 1 — 11 . C on sc ie nt io us ne ss 5. 30 1. 02 – .0 3 –. 03 – .1 7 .3 3 –. 14 – .3 4 .3 1 .2 1 .3 3 –. 13 .7 6 — 12 . E m ot io na l s ta bi lit y 3. 70 1. 22 .2 0 .2 5 –. 01 .1 9 .1 0 –. 05 – .1 2 .2 6 .1 7 .0 3 –. 04 .7 2 — 13 . E xt ra ve rs io n 5. 04 0. 96 .1 7 .1 4 .1 5 .0 8 .0 7 –. 09 .0 9 .2 1 .1 7 .2 1 .0 5 .0 2 .7 1 — 14 . A gr ee ab le ne ss 5. 72 0. 86 – .0 9 –. 10 .0 2 –. 07 – .0 8 .0 4 .0 1 .0 1 –. 09 – .1 2 .2 4 –. 11 .0 9 .8 3 — 15 . Ope nn es s to ex pe ri en ce 5. 22 0. 91 .1 1 .0 4 .0 7 .0 7 .1 1 –. 05 .0 5 .1 9 .1 3 .0 0 .1 3 –. 10 .2 8 .0 9 .7 9 — 16 . L if e sa tis fa ct io n 5. 34 0. 86 .3 2 .2 6 .2 0 .1 8 .1 9 –. 05 – .0 3 .3 9 .3 3 .1 4 .0 8 .2 5 .3 1 .0 8 .2 6 .7 3 — 17 . G PA 3. 22 0. 41 .1 1 .1 1 –. 05 .2 3 .0 4 –. 17 .1 2 .2 1 .2 1 .0 4 .3 0 .0 6 .1 6 –. 02 .2 3 .1 4 — — 18 . S el f- re po rt ed pe rf or m an ce 3. 77 1. 52 .2 1 .2 0 .0 5 .2 7 .0 7 –. 19 .0 1 .2 0 .2 1 .0 4 .2 5 .0 5 .1 9 –. 01 .3 3 .2 3 .6 6 — N ot e. I ta lic iz ed n um be rs in th e di ag on al in di ca te r el ia bi lit y co ef fi ci en ts ( al ph a) o f ea ch s ca le . r > .1 5, p < .0 5; r > .1 9, p < .0 1; r > .2 4, p < .0 01 . 206 The Journal of Social Psychology Of the Big Five personality factors, as expected, emotional stability and extraversion were positively related to active procrastination (r = .20, p < .01 and r = .17, p < .05, respectively). Contrary to our expectations, conscientiousness was not a significant negative predictor of active procrastination (r = –.03, ns), perhaps because of its strong positive relation with the ability-to-meet-deadlines dimension (r = .33, p < .001). Last, active procrastination had significant positive correlations with life satisfaction and self-reported performance (r = .31, p < .001 and r = .21, p < .01, respectively). However, unlike Chu and Choi’s (2005) results, the objective performance measure (i.e., GPA) was not significantly related to active procras- tination (r = .11, ns.), even though the direction was positive. Incremental Validity As a final step in construct validation, we examined the incremental valid- ity of the new scale of active procrastination to determine its unique added value in explaining relevant outcomes above and beyond existing personality measures, such as the Big Five personality factors. To this end, we conducted hierarchical regression analyses using life satisfaction, GPA, and self-reported performance as dependent variables. To provide a theory-driven, generalizable test of the incremental contribution of the four active procrastination dimen- sions, we entered them simultaneously in the second step of the hierarchical regression, following the first step that included the Big Five factors (Hunsley & Meyer, 2003). As presented in Table 3, results showed that the four dimensions of active procrastination explained significant additional variance of two of the three outcome measures (i.e., life satisfaction and self-reported performance, ∆R2 = .06, p < .05, and ∆R2 = .05, p < .05, respectively) after controlling for the effects of the Big Five personality factors. Specifically, life satisfaction was significantly predicted by intentional decision and ability to meet deadlines (β = .15 and .13, respectively, both ps < .05). Self-reported performance was pre- dicted by preference for pressure and ability to meet deadlines (β = .18 and .16, respectively, both ps < .05). We observed approximately the same amount of additional explained variance was observed when we used a composite score of active procrastination instead of the four-dimensional measures. None of these regression equations, such as homoscedasticity and normality of residuals, vio- lated basic assumptions for the analysis. The R2 change of .05 and .06 indicated that the active procrastination dimensions had a semipartial r ranging between .22 and .25, which falls between small and medium effect size (r = .10–.30; Cohen, 1992), even after controlling for the effects of Big Five factors. The results suggest that the new active procrastination scale possesses reasonable incremental validity and, thus, makes a distinct contribution to the understanding of key individual outcomes. Choi & Moran 207 Discussion The purpose of this study was to develop and validate a new measure of active procrastination that would allow this construct to be systematically inves- tigated and effectively incorporated into the literature. Given the prompt attention to this new construct in various disciplines (e.g., Alexander & Onwuegbuzie, 2007; Bernold, 2007; Bui, 2007; Hu et al., 2007; Howell & Watson, 2007), researchers appear willing to engage in substantial empirical efforts to investigate its implications within their domains of interest. At this early stage of construct development, it is imperative to possess a well-developed measure of active pro- crastination with sufficient reliability and validity because the use of inadequate measures presents a serious threat to both the interpretation of study results and the accumulation of knowledge of the phenomenon in question (Hinkin, 1998). To this end, expanding Chu and Choi’s (2005) initial measure of active pro- crastination, we assembled 40 items representing its four theoretical dimensions. Through exploratory and confirmatory factor analyses of survey data, we devel- oped a 16-item measure of active procrastination that confirms the four-dimen- sional structure of the construct. The new scale of active procrastination provides clear advantages over Chu and Choi’s initial measure in several respects. First, in contrast to the initial measure’s marginal reliability, the responses to the new scale clearly exhibited acceptable reliability on both the composite measure and the four individual dimensional measures of active procrastination. Second, unlike TABLE 3. Hierarchical Regression Analyses of Big Five Factors and Active Procrastination Predicting Individual Outcomes Self-reported Life satisfaction GPA performance Predictor Step 1 Step 2 Step 1 Step 2 Step 1 Step 2 Conscientiousness .03 .02 .30*** .26** .23** .18* Emotional stability .28*** .23** .08 .04 .07 .01 Extraversion .24** .19** .10 .09 .11 .07 Agreeableness .06 .09 –.11 –.09 –.09 –.06 Openness to experience .21** .19** .18* .17* .29*** .28*** Preference for pressure .09 .06 .18* Intentional decision .15* –.04 .07 Ability to meet deadlines .13* .10 .16* Outcome satisfaction .04 .02 –.08 R2 .20*** .26*** .15*** .17** .18*** .23*** Change in R2 .06** .02 .05* *p < .05. **p < .01. ***p < .001. 208 The Journal of Social Psychology the rather ambiguous and weak factor structure observed in the initial measure, the new scale clearly supported the four-dimensional factor structure, confirm- ing the underlying theoretical components of active procrastination. Third, in contrast with the original measure, the four dimensions of the new measure were represented by the same number of items and made comparable contributions to the suprafactor of active procrastination. These strengths of the new scale, along with the validity and reliability observed in the current sample of 185 participants, provide great flexibility for researchers who may want to focus on just one or two of the dimensions or on the overall level of active procrastination. This final measure can also be easily administered in various contexts (both academic and organizational settings) and facilitate a more sophisticated understanding of pro- crastination behavior than is currently available in the literature. In addition, this study further expanded the nomological network of the active procrastination construct by examining its relations with polychronicity and the Big Five personality dimensions. Reconfirming Chu and Choi’s (2005) finding, the present data indicated that active procrastination is distinct from traditional procrastination. Moreover, active and passive (i.e., traditional) pro- crastination measures showed quite different, often opposite, relations with other variables examined in this study (see Table 2). The present data further support thehypothesis that active procrastination is negatively related to highly struc- tured use of time, which may contribute to an increased perception of control of one’s time. It also supports the contention that active procrastinators tend to engage in multitasking, which likely necessitates continuous reorganization and reprioritization of their task activities. The present study also shows that active procrastination has significant relations to two of the Big Five personality factors. To actively procrastinate, individuals appear to need to possess a certain level of self-reliance and stability as well as active and energetic engagement with others and the task at hand. This is because escaping from preplanned activities and subjecting oneself to last-minute pressure is a risky behavior that requires self- confidence and energy. Overall, we believe that the present study paves the way for more rigorous empirical investigation of active procrastination. There are several directions for further research that could enrich the understanding of this new construct. First, both the present research and Chu and Choi’s (2005) study used undergraduate students as the study sample, which left the question open as to whether active procrastination can induce the same favorable effects in other groups of people. We speculate that most professional workers dealing with tight deadlines with substantial time pressure and frequent, unpredictable interruptions in their work (e.g., management consultants, professors, software engineers) may benefit from flexible time management behaviors such as active procrastination. In contrast, in relatively routine and predictable task situations, nonprocrastination, or a mono- chronic orientation to time, would likely be a better task strategy (Hecht & Allen, 2005). Future studies could explore the possibility that diverse requirements for Choi & Moran 209 task completion and productivity moderate the effect of active procrastination on individual well-being and performance. Second, researchers could investigate whether societal culture sets a bound- ary condition for the role of active procrastination. Typically in Western cultures, procrastination is regarded as a negative behavior that is indicative of laziness, leading to poor performance and satisfaction as well as negative self-image. Therefore, it is easy to understand why people in Western cultures would balk at the idea of a positive form of procrastination. However, in other cultures, people may perceive time differently (e.g., cyclical or curvilinear rather than linear), and they may be quite tolerant of slowness or lack of punctuality. In short, people from different cultures may possess different assumptions and views related to time flow, time structure, and temporal reference points of past, present, and future, all of which influence time-related perceptions and values and further prescribe time management behavior (Mosakowski & Earley, 2000). Last, because the construct of active procrastination was proposed recently (Chu & Choi, 2005), further expansion of its nomological network and ensuing theoretical elaboration of the construct is necessary. For example, given that active procrastination is driven by a strong self-regulatory process (Golwitzer & Bayer, 1999), it may have meaningful connections with such variables as locus of control, goal orientations, and other social cognitive processes associated with performance management. In addition to testing the validity of the active pro- crastination phenomenon in different cultural and professional contexts, future studies should adopt a longitudinal research design to investigate temporal fluc- tuations or developmental processes involved in active procrastination patterns. AUTHOR NOTES Jin Nam Choi is an associate professor of organizational behavior at the Graduate School of Business at Seoul National University, Korea. 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