prediction of the probability of successful first year ... · for students who completed 2 unit...
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PREDICTION OF THE PROBABILITY OF SUCCESSFULFIRST YEAR UNIVERSITY STUDIES IN TERMS OF
HIGH SCHOOL BACKGROUND: WITHAPPLICATION TO THE FACULTY OF ECONOMIC
STUDIES AT THE UNIVERSITY OF NEW ENGLAND
D.M. Dancer and H.E. Doran
No. 48 - September 1990
ISSN
ISBN
0 157-0188
0 85834 893 4
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General Background
This paper is motivated by informal observation over several years of first year students
in the Faculty of Economic Studies at the University of New England. A very casual
appraisal of students who have struggled has indicated that many of them had a poor
background in Mathematics as well as a fairly low level of achievement in the New South
Wales Higher School Certificate Examination.
A formal analysis of results could be a useful contribution to educational decision
making. In particular, estimating the important determinants of performance could sig-
nificantly improve the assessment of a student’s chances of success. It was considered that
factors which could influence the success rate of first year students would include the HSC
aggregate score, preparation in Mathematics and the type and location of schooling.
The aim of this investigation is to relate the probability of a student passing a range
of subjects to these ’background variables’ and this is achieved by using the technique of
probit analysis.
The Probit Model
The basic tool used in this paper is probit analysis. The probit model is a qualitative
response (QR) model in which the dependent or endogenous variable may only take the
discrete values 0 and 1. The particular form of the probit model used in this study is a
univariate binary QR model where the normal distribution is specified as the function F.
It is convenient mathematically to define the dichotomous random variable y which
takes the value of one if the event occurs and zero if it does not occur. It is assumed that
the probability of an event depends on a vector of independent variables m and a vector
of unknown parameters ~.
Amemiya (1981) writes the univariate dichotomous model as
p, = P(y~ = l)= F[I(m~,O)] i = 1,2, ...,n.
where F is the cumulative distribution function of some random variable and I(x~, 8) is a
scalar index and assumes the random variables y~ are independently distributed.
If a linear specification is chosen
and the model can then be written as
(i)
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The probit model follows from the specification in Equation 1 by choosing F to be the
cumulative distribution function (cdf) for a normal random variable. That is, F(.) =
To simplify the explanation of the probit model, a specific example will be used. It
could be hypothesized that a student’s probability of success is dependent on a number
of factors. The first factor and probably the most important factor to consider is the
HSC tertiary entrance score. This HSC score is used by the universities to determine a
student’s eligibility for a certain degree.
Another factor that is considered to have a bearing on the level of success is the level
of mathematics that a student undertakes at high school. The level of mathematics is
particularly relevant if the student is considering a Science or an Economics degree.
In some respects, probit analysis is analogous to regression analysis. Let us suppose
that we are interested in investigating the number of subjects passed. One way of ap-
proaching this problem would be to postulate that the number of subjects passed, Y,
could be regarded as a function of several variables. For example,
Y = f(HSC score, level of mathematics, place of school). (2)
The linear regression model may then enable an equation in the following form to be
estimated :-
Y = ¢~0 +/~ * X1 +/~2 * X2 + ¢~3 * X3 (3)
where
* X1 = HSC score
¯ X2 = level of mathematics completed at high school
* Xs = country or city school.
Note that if more than two levels of mathematics are being compared, then several dummyvariables would be needed to capture the differences between the levels. We emphasise
that such an approach could be used to calculate the average number of subjects passed
for any combination of the three variables.
Another problem that is of interest is to estimate the proportion of students who pass
two or more subjects. When analysing proportions or probabilities, probit analysis is
an appropriate technique. An approach similar to the regression problem can be used.
Again, a sample of students can be taken who have an HSC score, completed 2 UnitMathematics and attended a city school.
2
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These proportions could be interpreted as the probability that a student with certain
qualifications will pass at least two or more subjects. When probabilities are to be esti-
mated, the technique analogous to regression analysis is probit analysis. To illustrate this
technique, an example will be given.
For the sake of simpficity, consider students at a university who have enrolled in an
Economics degree. Let
HSC tertiary entrance score.Xli --
X21 = 1 if the student completed 2 Unit A Mathematics
= 0 if the student completed 2, 3 or 4 Unit Mathematics
X3i = 1 if the student attends a city high school
= 0 if the student attends a country high school
The variables X2i and X3i are dummy variables.
Define an index I[, given by
(4)
which is a single number summarising the values of X1, X2 and X3 for the ith individual.
Such an index, which can take any real value, can be converted to a probability by re-
flecting it in any cumulative distribution function. The probit model uses the distribution
function associated with a normal random variable. That is,
where Fx(.) isthe distribution function of a random variable X which is
Now
= P[X <_ 3"0 + 3"~ * Xli + 72 * X~i + 3"3 * Xz~]
= P[Z <_ (3"0 + 3"~ * X,, + 3"~ * X2, + 3"3 * ~) - ~]= P[Z <_ (5)
where Z ,-, N(O, 1) and
I~ - (3’0 - tz) + 3"~ ¯ Xli + 3"~ * X2i + 3"~ * X3i
That is,
I~ =/3o + ~ * X~i + 32 * X2i + fl~ * X~i. (6)
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Because of the arbitrary nature of the coefficients 7{ and/3i, it is always possible to choose
Fx(.) :where q~z(.) is the cumulative distribution function of the standardised normal random
variable.Consider some hypothetical values of/30, ~31,/32 and f13. Let 30 = -2.0,/31 = 0.01,
~2 = -1.5, ~33 = -0.5. Three individuals have been chosen to illustrate this example. The
first student has an ttSC score of 280, has completed 2 Unit A Mathematics and attended
a city high school. The second student has an HSC score of 300, has completed 2 Unit
Mathematics and attended a city high school. The third student has an HSC score of
350, has completed 3 Unit Mathematics and attended a country high school.
The index value for the first student is calculated as
-2.0 + 0.01 * 280 - 1.5 * 0 + -0.5 * 1 = -1.2.
Therefore,
P(Z <_ I~) = P(Z ! -1.2) = 0.12.
From Table 1, it can be seen that the probabihty that a student who has an HSC score of
280 with 2 Unit A Mathematics and has attended a city high school is quite low (0.12).
The probability that a student who has an HSC score of 300 with 2 Unit Mathematicsand has attended a city high school is 0.59. This indicates that this student hsa about a
50% chance of passing two or more subjects. The third student who has an HSC score
of 350 with 3 Unit Mathematics and attended a country high school has a very high
probability of passing two or more subjects at the end of first year at university. In the
Table 1: Probabihties of a Student Passing 2 or More Subjects
Student HSC Score Level of City or Index Proby
Mathematics Country School
1 280 2UA City -1.2 0.12
2 300 2U City 0.5 0.59
3 350 3U Country 1.5 0.93
above example, the coefficients, b0, bl, b2 and b3, were assigned arbitrary values. In reahty,
these numbers are always unknown, and must be estimated from the data.
The data for this project are in the form of a single observation on each decision maker.
This means that maximum likelihood methods must be used for estimation purposes. For
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a sample of T observations, the likelihood function is
(7)
where y~ = 1 or 0. The logarithm of the likelihood function is maximised using numer-
ical methods. The properties of the log likelihood function guarantee that the iterative
procedure will converge to the global maximum based on any suitable set of starting
values/3(0). Also the maximum likelihood estimators of the/3 parameters are consistent,
asymptotically efficient and asymptotically normally distributed.
In this project, the two events which are considered separately are ’The student passes
all his subjects ’ and ’The student passes all three main subjects’.
Data
The data for this study were obtained from two sources. The first source was the Admin-istrative Data Processing section of the University of New England (UNE) which provided
information on every student enrolled in the Faculty of Economic Studies in 1988. The
following information was provided:-
¯ the degree in which the student was enrolled
¯ the HSC aggregate mark
¯ each student’s examination results for 1988.
For some students who live interstate, the UNE calculates an equivalent HSC aggregatemark which was then subsequently used in the analysis.
The second source of data was a questionnaire sent out to M1 students with a 1988
student number in the Faculty of Economic Studies. This survey was a postal survey with
one follow up of those who had not replied the first time. Students were asked for the
following information:-
¯ State in which their education took place
¯ Highest level of Mathematics they attempted
¯ Highest level of Enghsh they attempted
5
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¯ Education at a state or a private school
¯ Town or city in which they completed their education
The students were asked to answer these questions for the last two years at high school.
On the basis of this information, the following variables are defined.
D~ = 1
= 0
D2 = 1
= 0
M1 = 1
= 0
M3 = 1
= 0
E1 = 1
= 0
School = 1
= 0
City = 1
= 0
HSC =
for Bachelor of Agricultural Economic Students
otherwise
for Bachelor of Financial Administration Students
otherwise
for students who completed 2 Unit A Mathematics at high school
otherwise
for students who completed 3 or 4 Unit Mathematics at high school
otherwise
for students who completed 2 Unit English at high school
otherwise
for students who attended a state high school
otherwise
for students who attended a city high school
otherwise
the HSC tertiary entrance score for the student.
The basic model postulated is
I = f(M1, M3, D1,D2, HSC, El, School, City) (s)
Results
In this analysis, we are concentrating primarily on estimating the probability that a
student will pass all subjects. To this end, a number of probit models are estimated
including various combinations of the variables M1, M2, D1, D2, El, HSC, School and
Gity. The results of these estimations are presented in Appendix A.
The main features of the empirical results are :-
¯ The HSC aggregate is highly significant statistically.
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The level of Mathematics and whether the student attended a country or city school
are nearly always significant.
With regard to Mathematics, once H$C aggregate is controlled, there appears to be no
difference between 2 and 3 Unit Mathematics students. As we have chosen the 2 Unit
group as base, we therefore omit the variable M3. Accordingly, for further interpretation,
we have selected the model
I = -2.4228 + 0.009725 HSC - 1.3452 Ml - 0.5471 City(0,887} (0.00973) (0.590) (0.259)
(9)
The probabilities which result from this index are shown in Figures 1 and 2 below, in
which probability is plotted agMnst HSC aggregate for city educated students (Figure 1)
and country educated students (Figure 2). Two points emerge very clearly front these
figures.
If a student enters the university with an HSC aggregate of 260 and 2 Unit Math-
ematics, then the probability of passing is approximately 0.52 for a student from a
country school and approximately 0.32 for a student from a city school. However, if
a student enters the university with an ttSC aggregate of 260 and 2 Unit A Mathe-
matics, then these probabilities drop dramatically to 0.1 and 0.03 respectively.
The effect of 2 Unit Mathematics on a student’s prospects is very marked. For
example, for a student to have an even chance of passing all subjects with only2 Unit A Mathematics, an tlSC aggregate of about 380 if the student is from a
country school and about 440 if the student is from a city school is required.
The implications of the model could also be interpreted from a different perspective.
In Figures 3 and 4, we display the results of 2 Unit Mathematics students(Figure 3) and
2 Unit A Mathematics students (Figure 4). This enables us to see the difference between
city and country educated students. It is apparent that country students have superiorperformance. Ra(her than inferring that a country education is superior, we suspect that
we are observing a ’living away froln home’ effect. It would be interesting to see a similar
analysis performed on students from a metropolitan university. Quite possibly the results
would be reversed. We note in passing that a perusal of Appendix A shows little evidence
that private or public school education has any effect on university results, at least in theFaculty of Economic Studies.
In addition to the above analysis, we carried out a similar analysis to assess the
probabifity of students passing the core subjects common to all three degrees - namely,
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Economics, Econometrics and Mathematics. The same broad conclusions emerge except
that now, while the Mathematics effect is numerically very large, it is not statistically
significant. The difference between country and city is no longer quite so marked.
Conclusion
This analysis has given rise to two main conclusions.
Students who enter with an HSC aggregate of under 300 have a very low probability
of passing all subjects. Such a conclusion has clear resource implications particularly
in an environment in which Government pressure is towards increasing acceptanceof poorly qualified students.
Mathematical preparation appears to be very important. There is a clear differen-
tiation between students who have at least 2 Unit Mathematics and those who do
not.
References
Amemiya T. (1985) Advanced Econometrics, Blackwell, Oxford.
8
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City Students
0.8
0.7
0.6
0.5
0.4
0,3
0.2
0.1
0,0
Legend¯ 2 Unit Mathematics
200 220 240 260 280 500 $20 540 360 380 400 420 440 460HSC Aggregafes
Figure 1: Students from City Schools Passing All Subjects
1.0 1
O.g
0.8
0.7 ~.
0.6~
0.5
0.4
0.3
0.2
0.1
0,0
Country Students
Legend¯ 2 Unit Mathematics= 2 Unit A Mafhemotics
200 220 240 260 280 500 320 340 360 580 400 420 440 460HSC Aggregate
Figure 2: Students from Country Schools Passing All Subjects
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1.0
0.9
0.7
0~6
0.5
0.4
0.3
0,2
0.1
Studenfs wlth 2 Unit Mathematics
¯ Country Students= City Students
0.0 I 1 I I I I ! I 1 I I I I200 220 240 260 280 500 320 340 360 380 400 420 440 460
HSC Aggregote
Figure 3: Students with 2 Unit Mathematics Passing All Subjects
SJudents with 2 Unit A Mathematics
1.0
0.8
0.7
0.6
0.4.1
0.3
0.2
0.1
0.0
Legend
Country StudentsClty Students
200 220 240 260 280 .~00 $20 540 360 580 400 420 440 460HSC Aggregote
Figure 4: Students with 2 Unit A Mathematics Passing All Subjects
10
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Results of the Different Probit Analysis
Table 2: The Variable ’Passing All Subjects’ vs Different Combinations
Const M1 M3 D1 D2 HSC E1 School
¯ ¯ ¯t
o
,tt ,tott*tt
¯ tt ot,t,ttottottott otott ,t¯ tt otott ot¯ tt otott ot¯ tt ,tott ot¯ tt ,tott ott,tt ,t¯ tt ott
¯
o
¯
¯
¯
¯
o
o
.tt
°t °tt
o
.tt,tt
,tt,tt,tt,tt,tt,tt,tt*tt*tt,tt,tt,ttott,tt,ttott
o
o
.t
.t
o
o
City R~
0.074
0.068
0.025
oft 0.0750.034
0.203
0.163
0.159
ott 0.146°tt 0.132
°t 0.213
°t 0.198
"t 0.1880.169
"t 0.2420.219
0.214
°t 0.255
0.219
0.247
° t t 0.272
°t 0.283
0.227
°tt 0.281
0.251
"t 0.289
Predict
0.661
0.637
0.637
0.653
0.637
0.710
0.645
0.669
0.661
0.669
0.685
0.710
0.694
0.669
0.718
0.702
0.710
0.726
0.710
0.726
0.702
0.726
0.669
0.726
0.742
0.726
11
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WORKING PAPERS IN ECONOMETRICS AND APPLIED STATISTICS
goe~di~ ~in2.omt ~od~e~. Lung-Fel Lee and William E. Griffiths,No. I - March 1979.
Howard E. Doran and Rozany R. Deem No. 2 - March 1979.
Willi~m Grlfflths and Dan Dao, No. 3 - April 1979.
D.S. Prasada Rao0 No. 5 - April 1979.
O~ o~ the ~eiqC~_d ~Za~ O&a~ Za an ~ ~~~~od~: H Dg0r_~ o~ ~ox~ o~ g~gcgen~, tloward E. Doran,No. 6 - June 1979.
Re/~ ~6q~ ~od2_~. George E. Battese andBruce P. Bonyhady, No. 7 - September 1979.
Howard E. Doran and David F. Williams, No. 8 - September 1979.
D.S. Prasada Rao, No. 9 - October 1980.
~h~ Do/~ - 1979. W.F. Shepherd and D.S. Prasada Rao,No. I0 - October !980.
~atag gOn~-~ and gaozus-Yecik~m Do2a to gatOnaLea ~az~~ ~u,w3.ixutu~ ~o~aad Neqo~ ~wu~ ~LaRa. W.E. Grlfflths andJ.R. Anderson, No. II - December 1980.
~ac&-O~-~ ~eaZ ia ~ ~a~z~rme o~ 7�~. !toward E. Doranand Jan Kmenta, No. 12 - April 1981.
~b~ Oad~z ~ui~aq~J~ ~ta/~acaa. H.E. Doran and W.E. Gri£fiths,No. 13 - June 1981.
Ze~ ~Ae go~o~_a ~,ar.e gadem and ~te ~o~uaq.Pauline Beesley, No. 14 - July 1981.
~o~ Doia. George E. Battese and Wayne A. Fuller, No. 15 - February1982.
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2
~)~. H.I. Toft and P.A. Cassidy, No. 16 - February 1985.
~t~ :Yeata ~ the Tazdkat .¢do~ab1~ent ~ ~!~e ~~~ ~od~.H.K. Doran, No. 17 - F~bruary 1985.
J.~.B. Guise and P.A.A. Beesley, No. 18 - February 1985.
g.E. Grtfftths and K. Surekha, No. 19 - August 1985.
~~ ~. D.S. Prasada ~ao, No. 20 - October 1985.
H.E. Doran, No. 21- November 1985.
R. Carter Hill and Peter J. Pope, No. 22 - November 1985.
~~ ~oa. gilliam E. Grlffiths, No. 23- February 1986.
~ ~ ~~. T.J. Coellt and G.E. Battese. No. 24-February 1986.
~~ ~~ ~ ~~ ~. George E. Battese and
Sohall J. Halik, No. 25- April 1986.
George E. Battese and Sohail J. ~allk, No. 26 - April 1986.
~~. George E. Battese and Sohatl J. Haltk, No. 27 - Hay 1986.
George E. Battese, No. 28- 3une 1986.
N~. D.S. Prasada Rao and J. Salazar-Carrillo, No. 29- August1986.
~~ ~ ~ Y~ ¢~ ~ ~. ~(I) ¢~ ~. ll.E. Doran,~.E. Grlffiths and P.A. Beesley, No. 30 - August 1987.
gi111am E. Griffiths, No. 31- November 1987.
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"3
Chris ~. Alaouze, No. 3~ - Sept.em[~er, 19BB.
G.E. Battese, T.J. Coelll a,ld T.C. Colby, No. 33--January, 19B9.
Tim J. Coelll, No. 34 - February, 1989.
Idllllam Grlfflths and Geo~ge Judge, No. 36 - Februagy, 1989.
~flanao¢~l~ o~ ~rtztiqdtZot[ WuteJ~ 1)~tq~ng 7_)qouq!~t. Chris N. Alaouze,No. 37 - April, 1989.
~~ ~ IVa~ ~oc~tt Tqo&~. Chris M. Alaouze, No. 38 -July, 1989.
~tl~ ?n,t~ ~tnea, t ~,~oqqammDW ~eatuati~a o~ Ya~ a~ ~a~,toqqinq.
Chris M. Alaouze and Campbell R. Fitzpatrick, No. 39- August, 1989.
SatUaa~ a~ ~i~k ~ u~ Yeemtnqt~ ~nnetat~t ~eqaeaaiona cmdDa~a. Guang II. Wan, William E. Grlfflths and Jock R. Anderson, No. 40 -September 1989.
tlhe O~ o~ ~apacU~ Yhardnq in Yteclw~tLc Dtlnan~c T,mqaaomd~Wo~ ~’hane.d ’.Reaea~ei]~ OpemU.e~. Chris H. hlaouze, No. 41 - November,1989.
~~ ~heorul and YimutatLott ~/pp~ea. William Grlfflths andHelmut L~tkepohl, No. 42 - Flarch 1990.
Howard E. Doran, No. 43- March 1990.
No. 44 - Flarch 1990.lloward E. l)ovan,
:Re~. lloward Doran, No. 45 - Hay, 1990.
Howard Doran and Jan Kmenta, No. 46 - Flay, 1990.
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E./~. Selval~a[ha~. No. ~.’[ -Sepl.e~be~0 1990.
II.E. l)oran, No. ~18- gepte~nber, 1990.
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