A panel-data study of the effect of student attendance on university performance.
Absenteeism from university classes is not a new phenomenon. The historian, Barbara W. Tuchman (1979, p.119) states that in the 14th century `dwindling attendance at Oxford was deplored in sermons by the masters'. In 14th century England, low attendance might reasonably have been attributed to war and pestilence; today the reasons are less obvious. For whatever reason, both in North America and Australia, substantial numbers of university students regularly skip classes, Romer (1993, p. 167) described absenteeism in economics subjects at three `relatively elite' United States universities as `rampant', having found that approximately one third of students were absent from class on a given day. Rodgers and Rodgers (2000, p. 17) report attendance rates in an Intermediate Microeconomic Theory class at an Australian university that range from 68.4 per cent in the first half of the semester to 54.5 per cent in the second half of the semester.
Several analyses of cross-section data have found a strong association between students' attendance and performance. Devadoss and Foltz (1996), Durden and Ellis (1995), Romer (1993), Park and Kerr (1990), and Schmidt (1983) report strong correlations in classes as diverse as agricultural economics and agribusiness, microeconomic principles, macroeconomic principles, intermediate macroeconomics, and money and banking. No study has established a causal relationship between attendance and performance, using experimental data and sound statistical methodology. A very recent paper by Marbuger (2001) tackled the problem of absenteeism by using a panel of observations on 60 students in an introductory microeconomics class at a medium-sized, state-funded, regional university in the United States. He estimated a probit model in which the probability of a student responding incorrectly to each question in a set of multiple-choice questions was related to the student's attendance at the lecture when the relevant material was covered. Marburger found that absenteeism increased the probability of an incorrect response by as much as 14 per cent.
This study is also based on observational data but, like Marburger's study, it employs panel data: observations were collected on each student's performance on several tests and his or her attendance at classes covering the material examined on those tests. (1) The availability of panel data allows the use of methodology that takes account of heterogeneity among students in unobservable variables that affect both attendance and performance, such as intelligence and motivation. Estimates of the effect Of attendance on performance so obtained are free of some of the bias that is present in estimates based on cross-section regression studies. (2)
The remainder of the paper is organised as follows. In Section 2 the model of the relationship between attendance and performance is presented. The data used to estimate the model are described in Section 3. In Section 4, the results of the estimation are presented and interpreted. Finally Section 5 summarises the conclusions of the study.
Academic performance is hypothesised to be a function of the student's class attendance and other variables, some of which are unobservable, such as the student's motivation and aptitude for the subject matter. These same variables are also likely to affect the student's propensity to attend class and lead to an upward bias in estimates of the effect of attendance on performance obtained from regression analyses of cross-section observations. If each student's attendance could be determined randomly, a regression of performance on attendance (and other relevant variables) would be able to detect a causal relationship, if one exists, and accurately estimate its magnitude. Experimental data of this type are difficult to obtain because of the requirement that students be treated equally. An alternative approach is to observe attendance rates that are self chosen and to model the unobserved heterogeneity among students using fixed-effects and random-effects regressions in which the dependent variable is performance by student i on assessment task t ([P.sub.it]) and the independent variable is attendance by student i at classes on which assessment task t is based ([A.sub.it]).
The models estimated in this paper include as independent variables dummy variables for all but one of T assessment tasks, [TEST.sub.1], [TEST.sub.2], ... [TEST.sub.T].
The fixed-effects model is:
(1) [P.sub.it] = [[alpha].sub.1] + [beta][A.sub.it] + [[gamma].sub.1][TEST.sub.1] +[[gamma].sub.2][TEST.sub.2] + ... + [[gamma].sub.T-1] [TEST.sub.T-1] + [[epsilon].sub.it]
where i=1,2, ... n; t=1,2 .... T. [[epsilon.sub.it] is an error term that is identically and independently distributed with E([[epsilon].sub.it]) = O, Var([[epsilon].sub.it]) = [sigma].sub.[epsion].sup.2] The coefficient, [beta], reflects the impact of attendance on performance in any given assessment task. (3)
The random-effects model is:
(2) [P.sub.it] = [alpha] + [beta][A.sub.it] + [[gamma].sub.1][TEST.sub.1] + [[gamma].sub.2][TEST.sub.2] + ... + [[gamma].sub.T-1][TEST.sub.T-1] + [delta][X.sub.i] + [[epsilon.sub.it] + [u.sub.i] where i=1,2, .. n; t=1,2, .. T and [X.sub.i] is a vector of time-invariant observable characteristics of student i. [[epsilon].sub.it] + ui is an error term with E([[epsilon].sub.it]) = E([u.sub.i]) = 0; Var([[epsilon].sub.it] + [u.sub.i]) = [[sigma].sub.[epsilon].sup.2] = [[sigma].sub.[upsilon].sup.2]; + Cov([[epsilon].sub.it],[u.sub.j]) = 0 for all i, t and j; Cov ([epsilon.sub.it], [[[epsilon].sub.js]) = 0 for t [not equal to] for t [not equal to] j; and Cov([u.sub.i], [u.sub.j]) = 0 for i [not equal to] j. Cov([[epsilon].sub.it] + [u.sub.i], [[epsilon].sub.is] + [u.sub.i]) =[rho] = [[sigma].sub.[upsilon].sup.2] / [[sigma].sup.2] for t [not equal to] s, that is, for a given student the errors on different assessment tasks are correlated because of their common component, u.
The time-invariant control variables included in the random-effects model are those suggested by other studies and those that seem intuitively plausible to experienced teachers of the subject matter. The first control variable is the student's average mark (out of 100) on other subjects taken during the same semester. It is a proxy for ability but it probably also reflects attendance in those other subjects. Assuming attendance is correlated across subjects, the inclusion of this variable is likely to result in an underestimate of the effect of attendance on performance in my class. (4) The second control is a dummy variable for students in their first year at university. Assuming the transition from high school to university requires some adjustment, it was hypothesised that first-year students would perform at a lower level than later-year students. The less able students tend to drop out after the first year of university studies, so that those who remain tend to be better academic performers. The third control is a dummy variable for students who are part-time. Many part-time students are mature-age, full-time workers with heavy demands on their time. The opportunity cost of time spent in class and in private study is higher for part-time students than for full-time students. Part-time students are likely, therefore, both to attend fewer classes and to perform at lower levels, than full-time students. The fourth control is a dummy variable for students who pay full fees. Other studies have found that private students perform better than students who are on scholarships or are supported by their parents, possibly because they are more motivated than students whose tuition is subsidised. The fifth control variable is a dummy variable for gender. Two dummy variables are included to reflect the type of degree undertaken by the student: a single degree, other than a Bachelor of Commerce, or a double degree. The omitted category is a Bachelor of Commerce degree. Finally the method of entry into the university is represented by six dummy variables, the omitted category being standard matriculation from an Australian secondary school. The included categories are (a) entry via another Australian university, (b) entry via an overseas tertiary educational institution, (c) articulation from an Australian TAFE (technical and further education) college, (d) special entry, such as mature age, (e) entry via a professional qualification or an institutional assessment or examination, and (f) entry according to `other' criteria.
The data used in this study were collected in a one-semester, introductory statistics subject taught to undergraduates at a medium-size Australian university. There were three 50-minute lectures per week for 13 weeks delivered to the class of approximately 200 students using Power Point presentations. Printed Power Point slides, with certain key words, calculations and diagrams omitted, were made available in the library and could be purchased at a modest price from the university bookshop. Each student was required to attend one 50-minute tutorial in each of Weeks 2 to 13. Tutorial groups consisted of 20 or fewer students. As tutorial preparation, students were instructed to attempt a problem set involving the application of material covered in lectures in the preceding week. Eight of the twelve tutorial meetings were held in a regular classroom where a tutor presented the answers to as many of the problems as time permitted and responded to students' questions. Students could mark their own work using an answer key, which was made available in the library at the beginning of the week following the tutorial in which the problem set was discussed. The remaining four tutorial meetings were held in a computer laboratory where students, with the help of their tutor, used a statistical package to generate output with which to solve statistical problems. Attendance was recorded at all tutorials.
There were three tests during the semester. The mid-semester test was based on the first six weeks of lectures and was held on Saturday at the end of Week 7. It was multiple-choice, and contributed 15 per cent of the total score. The tutorial test was worth 10 per cent and consisted of problems similar to those assigned as tutorial preparation. The computer test was worth 15 per cent and examined knowledge of the output generated by the statistical package used in the subject. The tutorial and computer tests were both held in Week 13. The final examination was worth 50 per cent and concentrated on material taught in Weeks 7 to 12. It consisted of both multiple-choice questions and problems. The remaining 10 per cent of the final score was contributed by unannounced short quizzes held at the end of 12 randomly chosen lectures, six in each half of the semester. The quizzes provided a mechanism for estimating attendance in the first and last six weeks of lectures.
Two weeks into the semester there were 229 students in the class (5), 31 (13.5 per cent) of whom later withdrew. (6) Nine of the remaining 198 students took none of the four assessment tasks. Another 20 students missed at least one of the progressive assessment tasks and had the weight attached to that task transferred to the final examination. Two students completed all progressive assessment but did not take the final examination. Therefore 167 students received scores for the four assessment tasks. These students contribute data to the balanced panel that are used in the econometric analysis reported in Section 4. Their characteristics appear in Column 1 of Table 1. The characteristics of the 22 students who completed some but not all assessment tasks appear in Column 2 of Table 1. These students, together with the 167 students who completed all assessment, provide data to the unbalanced panel of 189 students used in the econometric analysis. The characteristics of the nine students who missed all of the assessment tasks but did not withdraw from the course are given in Column 3 of Table 1. These nine students are not included in the econometric analysis.
Table 1 indicates that students who completed all assessment tasks attended 70.86 per cent of lectures in the first half of the semester, 64.27 per cent of lectures in the second half of the semester, 78.89 per cent of regular tutorials and 82.63 per cent of computer labs. These attendance rates are significantly higher than those of students who did not complete all assessment tasks. Lecture attendance fell in the second half of the semester (7) and performance on the final examination was lower than on the mid-semester test. (8)
Only three observable characteristics display significant differences between students who completed all assessment tasks and students who missed some or all assessment. The latter scored significantly lower on other subjects taken in the same semester as this introductory statistics subject. Students who missed some or all assessment were more likely to be part-time. (9) A larger percentage of those who missed all assessment were full-fee paying students. (10) The relative similarity of the three groups of students whose descriptive statistics are reported in Table 1 suggests that the econometric analysis that is based on the panel is unlikely to be biased by the necessary omission of data on students who did not complete all assessment tasks.
The fixed-effects model (FEM) and the random-effects model (REM) described in Section 2 were estimated by using a panel of data to which each student contributed at least one and at most four observations. The four observations were: (a) score on the mid-semester test and attendance at lectures in Weeks 1 to 6; (b) score on the final examination and attendance at lectures in Weeks 7 to 12; (c) score on the tutorial test and attendance at regular tutorials; and (d) score on the computer lab test and attendance at computer labs. The fixed-effects model was estimated using LIMDEP's least squares dummy variable routine and the random-effects model was estimated using LIMDEP's generalised least squares routine (Greene, 1998, pp.318-325). For comparison purposes, the OLS estimates are also reported. The results of four models estimated with the balanced panel appear in Table 2.
The coefficient on attendance is statistically significant at the 5 per cent level in all models reported in Table 2. The FEM indicates that attending an extra one per cent of classes increases performance in introductory statistics by approximately 0.05 percentage points. According to the REM, the increase is 0.10 percentage points. The coefficient in the OLS model (0.20) indicates a larger effect of attendance on performance than the other two models. This was to be anticipated because the OLS estimate is positively biased, whereas the FEM and REM models control for unobservable characteristics of students that are likely to affect both performance and attendance. (11) The F-test and Breusch and Pagan's Lagrange multiplier test indicate that the OLS model should be rejected in favour of the FEM and REM respectively. Hausman's test indicates that the FEM is preferred to the REM. Based upon the FEM, a student with the average attendance rate, which was approximately 74 per cent of all classes, is predicted to score 1.30 (26 times 0.05) points (out of 100) lower than a student who attended all classes. Based upon the REM, the loss would be 2.6 (26 times (0.10) points. Although statistically significant, the differential is quite small. (12)
Among the control variables included in the REM, only two are statistically significant at the 5 per cent level. First, the student's average score on other subjects taken in the same semester as introductory statistics has a positive effect on his or her score on introductory statistics. In fact, each additional one-point difference in this average score on other subjects between two otherwise identical students is associated with a difference of 0.99 points in introductory statistics. Second, students who gain `special entry' into the university are predicted to score approximately 15 points lower in introductory statistics than an otherwise identical student who matriculated into university from high school.
The results of the models estimated with the unbalanced panel appear in Table 3. The coefficient on attendance is statistically significant at close to the one per cent level in all models. The effect of attendance on performance estimated by using the unbalanced panel (Table 3) is slightly larger than in the corresponding model that was estimated by using the balanced panel (Table 2). For example, the coefficient on attendance in the FEM is 0.06 in Table 3, rather than 0.05 in Table 2, indicating that a student with average attendance of 74 per cent of all classes would score 1.56 (26 times 0.06) percentage points lower than a student who attended all classes.
Finally the sensitivity of the attendance coefficient to the exclusion from the data set of students with atypically low levels of attendance is investigated. The results in Table 4 apply to the majority of students, who are not chronically absent. Columns 1, 2 and 3 report the estimation of the OLS regression, the FEM, and the REM by using only those students who attended at least one of the eight regular tutorials, at least one of the four computer labs, and at least one of the six randomly chosen lectures in each half of the semester. Columns 4, 5, and 6 report the estimation of the OLS regression, the FEM and the REM by using only those students who attended at least one of the eight regular tutorials, at least one of the four computer labs, and at least two of the six randomly chosen lectures in each half of the semester.
All the results in Table 4 are as strong statistically as those obtained with the full panel. Again the FEM is the preferred model, but its coefficient is larger than in Tables 2 and 3. For example, the coefficient on attendance in the FEM is 0.13 (see Column 2 of Table 4), which indicates that a student with average attendance of 74 per cent of all classes would score 3.38 (26 times 0.13) percentage points lower than a student who attended all classes. This is large enough to make the difference of one letter grade for some students. (13)
This study has estimated the effect of absenteeism on performance in an introductory statistics class of about 200 business and economics students at a medium-size Australian university. Absenteeism from lectures and tutorials was common among these students. On average, students attended approximately 68 per cent of lectures during the semester, 71 per cent in the first half of the semester and 64 per cent in the second half of the semester. The average tutorial attendance rate was 80 per cent, 87 per cent in the first half of the semester and 74 per cent in the second half of the semester. Computer laboratories were better attended (83%) than regular tutorials (79%).
The results reported here are based on a panel of four observations per student, each observation pertaining to performance on a particular test and attendance at the set of classes covering material examined on that test. The methodology takes account of unobserved heterogeneity among students and in so doing constitutes an improvement over cross-section regression results reported previously. Both fixed-effects and random-effects regression models were estimated and the fixed-effects model was judged to be superior. It was able to `explain' more than 70 per cent of the variation in performance among students on four different tests. Attendance was found to have a small, but statistically significant, effect on performance. A one per cent increase in attendance was found to result in an increase of between 0.05 and 0.13 points out of 100. This means that a student with average attendance of 74 per cent of classes would score between 1.3 and 3.4 percentage points lower than an otherwise identical student with perfect attendance. Although modest in size, this forfeited score is large enough to make the difference of one letter grade for some students. One explanation for the small size of the effect of attendance on performance could be the fact that the students in the class reported had access to printed versions (with `gaps') of the Power-Point slides that were presented in lectures. This may have both encouraged absenteeism and contributed to the ease with which students could substitute private study for lecture attendance.
Finally the total effect of attendance on performance may be greater than its impact in one subject suggests. When a subject is a prerequisite for others, the knowledge foregone through absenteeism in the first subject may have negative consequences for performance in subjects that build upon that knowledge.
academic achievement economics education performance factors attendance learning university outcome assessment
Table 1 Descriptive statistics Completed Completed Completed all some no assessment assessment assessment (1) (2) (3) Mean mid-semester test score (100) 62.69 52.34 ** n.a. Mean tutorial test score (100) 64.49 44.63 *** n.a. Mean lab test score (100) 64.15 51.13 * n.a. Mean final exam score (100) 53.65 25.88 *** n.a. Total weighted score (100) 57.67 n.a. n.a. Mean % lectures attended in Weeks 1-6 70.86 49.62 *** 14.82 *** Mean % lectures attended in Weeks 7-12 64.27 31.95 *** 1.85 *** Mean % regular tutorials attended 78.89 53.98 *** 27.78 *** Mean % labs attended 82.63 57.95 *** 16.67 *** Average mark on other subjects (100) 61.85 48.63 *** 29.77 *** Percentage in 1st year 44.91 36.36 44.44 Percentage part-time students 34.13 50.00 66.67 * Percentage paying full fees 12.57 9.09 44.44 ** Percentage male 60.48 72.73 66.67 Percentage Bachelor of Commerce 83.83 86.36 66.67 Percentage other single degree 6.59 9.09 11.11 Percentage double degree 9.58 4.55 22.22 Percentage entry via final year of secondary school 27.54 27.27 11.11 Percentage entry via higher educ. instit. (Au) 16.77 13.64 22.22 Percentage entry via higher educ. instit. (o/s) 1.80 4.55 00.00 Percentage entry via TAFE 16.17 9.09 11.11 Percentage entry via special entry 1.80 4.55 00.00 Percentage entry via prof. or instit. exam 12.57 27.27 11.11 Percentage entry via other method 23.35 13.64 44.44 Number of students 167 22 9 *** Significantly different at the 1% level from the students who completed all assessment tasks ** Significantly different at the 5% level from the students who completed all assessment tasks * Significantly different at the 10% level from the students who completed all assessment tasks Table 2 Effect of attendance on performance: Balanced panel of 167 students OLS FEM Coeff (P-value) Coeff (P-value) Model (1) (2) Constant: 40.92 (0.0000) Attendance 0.20 (0.0000) 0.05 (0.0474) TEST 1 7.74 (0.0002) 8.71 (0.0000) TEST 2 7.94 (0.0002) 10.10 (0.0000) TEST 3 6.86 (0.0013) 9.57 (0.0000) Av. score on other subjects 1st year student Part-time student Full-fee paying Male student Course: Other single degree Course: Double degree Entry: higher educ. (Australia) Entry: higher educ. (overseas) Entry: TAFE Entry: special entry Entry: instit or prof. exam. Entry: other R-sq 0.1286 0.7251 R-sq (adj) 0.1234 0.6310 F 24.47 (0.0000) 7.71 (0.0000) REM REM + Controls Coeff (P-value) Coeff (P-value) Model (3) (4) Constant: 47.50 (0.0000) -9.77 (0.1993) Attendance 0.10 (0.0000) 0.06 (0.0033) TEST 1 8.41 (0.0000) 8.61 (0.0000) TEST 2 9.44 (0.0000) 9.89 (0.0000) TEST 3 8.74 (0.0000) 9.31 (0.0000) Av. score on other subjects 0.99 (0.0000) 1st year student -0.29 (0.9112) Part-time student 3.67 (0.1470) Full-fee paying 5.78 (0.1092) Male student -2.12 (0.3066) Course: Other single degree -3.51 (0.3918) Course: Double degree 1.58 (0.6526) Entry: higher educ. (Australia) -0.27 (0.9317) Entry: higher educ. (overseas) 0.71 (0.9286) Entry: TAFE -4.93 (0.1484) Entry: special entry -15.41 (0.0431) Entry: instit or prof. exam. -4.34 (0.2352) Entry: other -3.03 (0.3324) R-sq 0.1286 0.3950 R-sq (adj) F Notes: No. of observations = 668 F test of FEM (column 2) versus OLS (column 1): 6.495 (P-value=0.0000) Lagrange Multiplier test of REM (column 3) versus OLS (column 1): 303.81 (P-value=0.0000) Hausman test of FEM (column 2) versus REM (column 3): 17.73 (P-value=0.0014) Table 3 Effect of attendance on performance: Unbalanced panel of 189 students OLS FEM Coeff (P-value) Coeff (P-value) Model (1) (2) Constant: 38.44 (0.0000) Attendance 0.22 (0.0000) 0.06 (0.0121) TEST1 8.37 (0.0000) 9.89 (0.0000) TEST2 8.13 (0.0001) 10.33 (0.0000) TEST3 7.33 (0.0005) 10.06 (0.0000) Av. score on other subjects 1st year student Part-time student Full-fee paying Male student Course: Other single degree Course: Double degree Entry: higher educ. (Australia) Entry: higher educ. (overseas) Entry: TAFE Entry: special entry Entry: instit. or prof. exam Entry: other R-sq 0.1494 0.7276 R-sq (adj) 0.1446 0.6270 F 31.09 0.0000) 7.23 (0.0000) REM REM + Controls Coeff (P-value) Coeff (P-value) Model (3) (4) Constant: 43.90 (0.0000) 1.28 (0.8454) Attendance 0.12 (0.0000) 0.07 (0.0007) TEST1 9.27 (0.0000) 9.82 (0.0000) TEST2 9.55 (0.0000) 10.21 (0.0000) TEST3 9.07 (0.0000) 9.93 (0.0000) Av. score on other subjects 0.81 (0.0000) 1st year student -0.50 (0.8431) Part-time student 2.88 (0.2344) Full-fee paying 4.42 (0.2192) Male student -2.69 (0.1879) Course: Other single degree -5.05 (0.2005) Course: Double degree 2.35 (0.5022) Entry: higher educ. (Australia) -0.29 (0.9260) Entry: higher educ. (overseas) -6.90 (0.3505) Entry: TAFE -6.64 (0.0460) Entry: special entry -11.34 (0.1060) Entry: instit. or prof. exam -5.94 (0.0869) Entry: other -3.88 (0.2082) R-sq 0.1494 0.3829 R-sq (adj) F Notes: No. of observations = 713 F test of FEM (column 2) versus OLS (column 1): 5.87 (P-value=0.0000) Lagrange Multiplier test of REM (column 3) versus OLS (column 1): 300.3 (P-value=0.0000) Hausman test of FEM (column 2) versus REM (column 3): 23.49 (P-value=0.0001) Table 4 Sensitivity of the effect of attendance on performance to students included in the panel OLS FEM REM Coeff (P-value) Coeff (P-value) Coeff (P-value) (1) (2) (3) Estimated using 136 students with more than 0% attendance in each component Model Constant: 31.33 (0.0000) 41.08 (0.0000) Attendance 0.31 (0.0000) 0.13 (0.0004) 0.18 (0.0000) TEST 1 7.47 (0.0011) 8.19 (0.0000) 7.99 (0.0000) TEST 2 9.58 (0.0000) 10.32 (0.0000) 10.11 (0.0000) TEST 3 8.04 (0.0005) 9.88 (0.0000) 9.35 (0.0000) R-sq 0.1560 0.7390 0.1560 R-sq (adj) 0.1498 0.6492 F 24.91 (0.0000) 8.23 (0.0000) Notes: No. of observations = 544 F test of FEM (column 2) versus OLS (column 1): 6.684 (P-value=0.0000) Lagrange Multiplier test of REM (column 3) versus OLS (column 1): 258.45 (P-value-0.0000)) Hausman test of FEM (column 2) versus REM (column 3): 12.38 (P-value=0.0147) OLS FEM REM Coeff (P-value) Coeff (P-value) Coeff (P-value) (4) (5) (6) Estimated using 121 students with more than 25% attendance in each component Model Constant: 26.61 (0.0000) 42.01 (0.0000) Attendance 0.36 (0.0000) 0.11 (0.0098) 0.17 (0.0000) TEST 1 7.09 (0.0037) 7.43 (0.0000) 7.34 (0.0000) TEST 2 9.90 (0.0001) 9.85 (0.0000) 9.86 (0.0000) TEST 3 8.74 (0.0004) 10.16 (0.0000) 9.80 (0.0000) R-sq 0.1385 0.7335 0.1385 R-sq (adj) 0.1313 0.6414 F 19.25 (0.0000) 7.97 (0.0000) Notes: No. of observations = 484 F test of FEM (column 2) versus OLS (column 1): 6.678 (P-value=0.0000) Lagrange Multiplier test of REM (column 3) versus OLS (column 1): 220.33 (P-value=0.0000) Hausman test of FEM (column 2) versus REM (column 3): 17.02 (P-value=0.0019)
I would like to thank two anonymous referees for their comments on an earlier draft of this paper.
(1) To my knowledge, only one other study has used Australian panel data. It is reported in an unpublished working paper by Rodgers and Rodgers (2000).
(2) Although my study is of just one class in one faculty at one university during one semester, when considered in conjunction with results from other studies it contributes to an informed judgement as to the seriousness of absenteeism in universities.
(3) Interactions between attendance and the assessment tasks were also included in the models to allow the effect of attendance on performance to be different for the various assessment tasks.
(4) This point is made by Romer (1993, p.172) and by Park and Kerr (1990, pp.105-108).
(5) In the first two weeks of each semester, a considerable amount of subject sampling takes place as students finalise decisions about which subjects to take. Students can drop subjects and avoid fees until the middle of the fifth week of the semester; they can drop without having an F recorded on their academic transcript prior to the end of Week 8.
(6) Only four of these students completed any of the progressive assessment tasks before withdrawing.
(7) Attendance at tutorials (regular plus labs) was also lower in the second half of the semester (73.55 per cent) compared with the first half (86.53 per cent).
(8) Correlation coefficients between attendance rates in the various components of the course based on the 167 students in the balanced panel are:
Attendance correlations Lect Lect Wk1-6 Tuts Labs (Wk7-13) Lect (Wk 1-6) 1.00 Tuts 0.37 1.00 Labs 0.29 0.46 1.00 Lect (Wk 7-13) 0.76 0.42 0.41 1.00
Correlation between performance in the various components of the course based on the 167 students in the balanced panel are:
Performence correlations Mid-s Tut Lab Final test test test exam Mis-s test 1.00 Tut test 0.54 1.00 Lab test 0.49 0.61 1.00 Final exam 0.67 0.67 0.68 1.00
(9) In this paper, a part-time student is defined as a student taking less than the normal load of 24 credit points per semester.
(10) In the Australian context at this time most full-fee-paying students were international students.
(11) Multicollinearity does not appear to be a problem. The correlations among the independent variables in Columns 1, 2 and 3 of Table 2 are:
Attend Test 1 Test 2 Test 3 Attend 1.00 Test 1 -0.07 1.00 Test 2 0.10 -0.33 1.00 Test 3 0.17 -0.33 -0.33 1.00
The largest correlations among the control variables in Column 4 are: r(attendance, average score on other subjects) = 0.53 r(1st year student, part-time student) = -0.43 r(full-fee paying, entry by higher education overseas) = 0.38 r(1st year student, entry by institute or professional exam) = -0.35 r(full-fee paying, entry by `other' method) = 0.32 r(part-time, entry via TAFE) = 0.30 All but six of the remaining correlations are less in absolute value than 0.20.
(12) The models were also estimated with interactions between attendance and the three dummy variables for the assessment tasks. None of the coefficients on the interactions was significant at the 5 per cent level.
(13) The models in this paper assume that performance in a later component (such as the final exam) depends only on attendance in classes when the subject matter of the later component was covered (Weeks 7-12), not on attendance in earlier classes (Weeks 1-6). To the extent that this assumption is untrue, the total effect of attendance on performance may be greater than results in this section suggest.
Devadoss, S. & Foltz, J. (1996). Evaluation of factors influencing student class attendance and performance. American Journal of Agricultural Economics, 78(3), 499-507.
Durden, G. C. & Ellis, L. V. (1995). The effects of attendance on student learning in principles of economics. American Economic Review, 85(2), 343-346.
Greene, William H. (1998). Limdep, Version 7.0, user's manual (Rev. ed.). New York: Econometric Software.
Marburger, Daniel R. (2001). Absenteeism and undergraduate exam performance. Journal of Economic Education, 32(2), 99-109.
Park, Kang H. & Kerr, Peter M. (1990). Determinants of academic performance: A multinomial logit approach. Journal of Economic Education, 2(2), 101-111.
Rodgers, John L. & Rodgers, Joan R. (2000). An investigation into the academic effectiveness of class attendance in an intermediate microeconomic theory class (Working paper). Wollongong: University of Wollongong, Department of Economics. (http: www.uow.edu.au~jrrodger)
Romer, David. (1993). Do students go to class? Should they?Journal of Economic Perspectives, 7(2), 167-174.
Schmidt, Robert. (1983). Who maximizes what? A study in student time allocation. American Economic Review, 73(2), 23-28.
Tuchman, Barbara W. (1979). The distant mirror. London: Macmillan.
Dr Joan Rodgers is in the Department of Economics, University of Wollongong, Northfields Avenue, Wollongong, New South Wales 2522.
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|Publication:||Australian Journal of Education|
|Article Type:||Statistical Data Included|
|Date:||Dec 1, 2001|
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