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http://www.tandfonline.com/loi/cshe20Students' expectations of debt
in UK higher education Ray BachanaaBrighton Business School ,
University of Brighton , Brighton , UK Published online: 16 Jan
2013.To cite this article: Ray Bachan , Studies in Higher Education
(2013): Students' expectations of debt in UK higher education,
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2. Studies in Higher Education 2013, 126, iFirst ArticleStudents
expectations of debt in UK higher education Ray Bachan*Downloaded
by [University of Westminster - ISLS] at 13:11 05 December
2013Brighton Business School, University of Brighton, Brighton, UK
The funding of students in UK higher education (HE) has undergone
radical reform over the past two decades. Using a unique dataset,
this paper investigates student expectations of debt. We nd that a
students gender, ethnicity, and year of study play an important
role in determining their expected debt. Students in receipt of
nancial support from their parents and those with part-time jobs
anticipate a lower level of debt. We also nd that the higher a
student discounts future income, the greater their expected debt,
and the more risk averse a student the lower the expected debt. Our
ndings also suggest that a students expected earnings
post-graduation has a positive impact on current debt. If the level
of student debt which is expected to rise in the future compromises
access to HE, then the close targeting of student nancial aid is
warranted and an equitable repayment framework needs development.
Keywords: student debt; debt expectations; higher education;
tobitIntroduction The UK higher education sector has grown rapidly
over the last 50 years. This expansion was particularly evident in
the 1960s in the wake of the publication of the Robbins Report
(1963), which created a rst wave of new universities, and in 1992
following the introduction of the Further and Higher Education Act,
when former polytechnics were granted university status. A key
feature of this expansion was to widen participation rates amongst
young adults from disadvantaged socioeconomic backgrounds and to
encourage participation of individuals from families with no
previous participation in higher education. The policy was given
major impetus in September 1997 when the then prime minister
declared a desire to increase the higher education participation of
young adults by the next century.1 The government set out to widen
and increase higher education participation to 50% in the 1730 year
age category by 2010 (Department for Education and Skills 2003a,
57). Recent gures suggest that initial participation rates for all
17- to 30-year-olds in UK higher education in 2010/ 2011 were about
47%; up from about 42% in 2006/2007 (Department for Innovation,
Universities, and Skills 2012).2 The rapid expansion of the UK
higher education sector and the desire to widen participation,
particularly in the 1990s, led to a funding crisis and the adoption
of student loans as an alternative method for funding student
higher education (Barr and Crawford 1998). Under such a system it
was envisaged that the limited public funds available for student
support should be targeted on those whose personal nancial
circumstances *Email: [email protected] ISSN 0307-5079 print/ISSN
1470-174X online 2013 Society for Research into Higher Education
http://dx.doi.org/10.1080/03075079.2012.754859
http://www.tandfonline.com 3. Downloaded by [University of
Westminster - ISLS] at 13:11 05 December 20132R. Bachancould hinder
access to higher education. Student loans were introduced in
1990/1991 to reduce the public subsidy towards student living
costs, with the remainder provided by a combination of educational
grants, bursaries, and parental contributions. Over time these
loans gradually replaced the existing maintenance grant and by the
academic year 1996/1997 the maximum loan accounted for 50% of the
grant. In 1998 mandatory grants were replaced by income-assessed
loans and new entrants to UK higher education received all their
maintenance allowance in the form of an income-assessed loan. At
the same time means-tested tuition fees were also introduced. The
2004 Higher Education Act viewed student loans as a means by which
students, after graduation, could repay their tuition fees. In the
academic year 2006/2007 new students attending higher education
institutions in England and Northern Ireland were charged a
variable fee of up to GBP3000 as a contribution to the cost of
their tuition. Students were given the option to take out a
tuition-fee loan to cover these extra costs. Tuition fees were
raised incrementally in line with ination and by 2010/ 2011 the
standard fee for full-time UK-domiciled students was GBP3290 set to
rise to a maximum of GBP9000 per annum in 2012/2013 (Browne 2010).
These changes in student nancial support meant that graduate
indebtedness was expected to rise considerably and particularly
from 2006/2007 onwards. Nevertheless, advocates of student loans
often argue that students are the main beneciaries of higher
education (e.g. in terms of enhanced future earnings) and should
contribute to its cost (Barr 2004; Friedman and Friedman 1980;
Glennerster et al. 1968). This argument is grounded in human
capital theory (Becker 1993) which assumes that students are able
to rationally assess the cost and benets of investing in human
capital (post-compulsory education). Such investment is expected to
enhance future productivity which in turn raises the individuals
future labour market earnings. If this assumption holds then one
may expect students in general to have a positive attitude towards
using loans as a means of nancing their higher education. This may
be true for students who expect high future earnings with a low
risk of unemployment. Thus the level of debt students anticipate by
the end of their studies may reect the higher future earnings they
expect in the graduate labour market. Several UK studies have found
evidence of substantial returns to higher education qualications
(Harkness and Machin 1999; Blundell et al. 2000; Bratti, Naylor,
and Smith 2007), which is consistent with international evidence
(Psacharopoulos and Patrinos 2004). However, the evidence is more
mixed as to whether or not students can form realistic expectations
of their future earnings. For the UK, Jerrim (2011) nds that
rst-year full-time students over-estimate their expected starting
salary by 20% and expectations become more realistic over time with
nal-year students overestimating their starting salary by about
15%. Brunello, Lucifora, and Winter-Ebmer (2004) found that
business and economics students in 10 European countries also tend
to over-estimate their future earnings, but Dutch and US students
in contrast made more accurate predictions (Webbink and Hartog
2004; Dominitz and Manski 1996; Betts 1996). There is another
strand of literature which interprets a system of student loans,
and the fear of indebtedness, as a potential barrier to access to
higher education. This is particularly evident for potential
students from lower socioeconomic groups, which may compromise the
stated policy objective to widen participation (Connor et al. 2001;
Knowles 2000; Callender 2003; Callender and Jackson 2005; Pennell
and West 2005). Moreover, there is evidence that nancial support
for students is inadequate (Callender and Wilkinson 2003), which
can contribute to rising student 4. Studies in Higher
Education3debt. Government concern over the perception of student
debt and participation in higher education was highlighted in the
lead up to the 2004 Higher Education Act (Department for Education
and Skills 2003b). Indeed in 2001, the then Secretary of State for
Education, Estelle Morris, highlighted the issue of student debt
and its negative impact on widening participation in higher
education:Downloaded by [University of Westminster - ISLS] at 13:11
05 December 2013I recognise that for many lower-income families the
fear of debt is a real worry and could act as a bar to higher
education. I want to make sure that our future reform tackles this
problem. (Department for Education and Skills 2001)3Furthermore,
the expectation of a high level of indebtedness can have further
unintended consequences especially for those students from
disadvantaged socioeconomic groups and students with limited
nancial support from their parents. For instance, it can
potentially reduce the time these students devote to study through
taking on paid part-time employment by necessity (Purcell and Elias
2010),4 which can adversely affect academic achievement (Ford et
al. 1995; Humphrey 2006; Brennan et al. 2005; Callender 2008).
Evidence also suggests that the fear of debt can affect a students
desire to continue in higher education (Davies and Elias 2003;
Yorke and Longden 2008) and future labour-market choices (Purcell
and Elias 2010). Studies in the United States also nd that nancial
pressure is positively associated with term-time working which can
have a detrimental effect on academic performance and future
choices (Strinebrickner and Strinebrickner 2003; Chapman and
Lounkaewa 2010; Kalenkoski and Pabilonia 2010; Zhang 2010;
Scott-Clayton 2012). The foregoing review suggests that changes in
public nancial support for students in UK higher education have
impacted student indebtedness, the student experience and
performance, and their future career choices. It is not surprising
that rising student debt has become a major issue of public
concern. However, the determinants of student debt expectations are
relatively under-researched in the UK, although several studies
have focussed on student attitudes to debt (see for example, Davies
and Lea 1995; Callender 2003; Brennan et al. 2005; Callender and
Jackson 2005; and Johnson et al. 2009). A notable exception is the
study by Purcell and Elias (2010) who explored the extent to which
nal-year students worried about debt using OLS regression analysis.
They nd evidence that male students are less fearful of
indebtedness compared to their female counterparts and higher
expected earnings on graduation lessened the extent of these
worries. In addition, they found students were more fearful of debt
in their nal year of study than they were in their rst. This study
contributes to the literature in several important ways. First, it
uses unique survey data to examine a variety of factors expected, a
priori, to inuence student debt expectations. The identication of
these factors is important from a policy perspective, particularly
when considering the targeting of student nancial support and the
design of debt repayment schemes. Second, the study examines the
impact that students attitudes to debt and risk and their future
wage expectations have on their expected debt during their period
of study. Third, this study offers a novel contribution to the
sparse literature that exists on the determinants of student debt
expectations. This paper is organised as follows. The next section
presents a brief background to the current state of student debt in
UK higher education. This is followed by a description of the data,
and then an outline of the statistical methodology employed. The
penultimate section presents the results of the empirical analysis,
and the nal section provides some conclusions. 5. Downloaded by
[University of Westminster - ISLS] at 13:11 05 December 20134R.
BachanStudent debt in the UK Student debt 1990/1991 to 2005/2006
Figure 1 shows that the average loan taken out by eligible
students, domiciled in England and Wales, increased considerably
over the period 1990/1991 to 2005/2006. We note that in the
academic year 1990/1991, when maintenance loans were introduced,
the average student loan was GBP390 in 1991 prices, and over the
decade to1998/1999 increased to GBP1509 in real terms as loans
replaced maintenance grants. Between 1998/1999 and 1999/2000 the
maintenance allowance was replaced by a means-tested loan and the
real average value of the loan increased by just over 33%. By the
academic year 2005/2006, the average student loan stood at GBP2338.
This increase in the size of the average loan was also accompanied
by an increase in the number of students taking out loans. In the
academic year 1990/1991, 180,200 students secured a loan, which
represented a 28% take-up rate across all eligible students. By
1999/2000, 699,700 students obtained a loan, representing a 72%
take-up rate which rose to 80% representing 880,700 students by
2005/2006 (Student Loans Company). These trends were anticipated
given the changes in student funding arrangements in England and
Wales. Surprisingly, given the growing public concern over student
debt, there is a dearth of ofcial statistics on the level of actual
student debt post-graduation between 1990/ 1991 and 2006/2007. The
Barclays Bank Graduate Debt Survey (2005), covering the period 1994
to 2004, showed that student debt for new graduates increased in
real terms by a factor of 3.7 from GBP2047 in 1994 to GBP9653 by
2004. The Natwest survey (2007) suggested that in real terms
student debt increased by aFigure 1. Average student loan (GBP)
1990/19912005/2006 (1991 = 100). English- and Welsh-domiciled
students. Source: Student Loans Company available at
http:www.slc.co.uk/ and authors own calculations. 6. Studies in
Higher Education5Downloaded by [University of Westminster - ISLS]
at 13:11 05 December 2013factor of just over 3.5 between 2000 and
2006 in 2005 real student debt was GBP8789 and in 2006 it was
GBP8929 (see Bolton [2009] for details). These surveys are not
directly comparable but illustrate the increase in student debt
between 1994 and 2006 (see Figure 2). Data from other surveys
broadly support these trends. The Push survey (2007) showed average
student debt remaining static or even falling in 2004 and 2005, and
the Unite survey (2007) revealed a small decline in average debt
among students in 2005. Callender and Wilkinson (2003) and
Callender and Kemp (2000) report that average student debt amounted
to GBP8666 in 2003 2.5 times higher than for those graduating in
1998 and 3.5 times higher than for those graduating in 1996.
Student debt post 2006/2007 Figure 3 reveals that between the
period 2006/2007 to 2010/2011 the average maintenance loan
decreased by about 4.6% and tuition fee loans remained relatively
constant in real terms, which is due in part to the increase in the
maximum tuition fee institutions were permitted to charge. Overall,
the average level of total student public borrowing decreased in
real terms by about 3%. It is also worth noting that the number of
student borrowers increased from 2.9 million in 2008/2009 to 3.2
million in 2009/2010 (Student Loans Company 2010). There is very
little ofcial UK data on the level of debt experienced by graduates
who enrolled in the academic year 2006/2007 or later. The 2007/2008
Student Income and Expenditure Survey, covering only
English-domiciled students, found that student loans made up 88% of
all student borrowing and average debt for nal-yearFigure 2.
Average student debt (GBP) 19942006 (1991 = 100). English-domiciled
students. Note: It should be noted that the gures reported above do
not apply to students who were liable for variable tuition fees.
The data for both series were derived from a survey of graduates
carried out 618 months after graduation. Source: P. Bolton (2009)
and authors own calculations. 7. Downloaded by [University of
Westminster - ISLS] at 13:11 05 December 20136R. BachanFigure 3.
Average maintenance loan and tuition fee loan (GBP) (1991 = 100).
England 2006/ 20072010/2011. Note: These gures represent awards to
English-domiciled students who entered university in November of
the relevant academic year irrespective of where they study.
Source: Students Loans Company, statistical rst release (November,
various years)full-time students graduating in 2008, who were not
part of the new student funding regime, was estimated to be GBP7783
(Johnson et al. 2009). Purcell and Elias (2010), using more recent
data, report that full-time UK students graduating in 2009
anticipate an average debt of about GBP15700 on graduation.
However, the Push survey (2010) estimated that students graduating
in 2009 expected a greater amount of debt totalling GBP22,000 on
average, and those graduating in 2010 or 2011 reckoned to be in
debt by an average amount of GBP23,000 and GBP24,700 respectively.
The portrait that emerges from this evidence is a signicant
increase in student expected indebtedness from 2009 onwards. It is
worth noting that international evidence on the debt students
expect on graduation is rare and studies often focus on the
repayment of debt post-graduation (see for example, Shen and
Zilderman 2009; Chapman and Lounkaewa, 2010; Chapman and Sinning,
2011). Usher (2005), however, reports a wide variation in student
debt burden post-graduation across eight countries including the
UK. The study nds that UK students have the fourth-highest debt at
graduation and only Swedish, Canadian, and US students having
higher debts. Recent evidence for the United States suggests that
students graduating in 2009 from private not-for-prot higher
education institutions who relied on student loans to fund their
undergraduate studies had an average debt of USD26,200 (GBP16,725),
and those graduating in 2010 an average debt of USD28,100
(GBP18,175) (College Board 2011).5 It is not easy to compare these
gures with student debt in the UK, but if student debt expectations
are realised then these gures may suggest that UK graduates will be
at least as indebted as their US counterparts in the near future.
8. Downloaded by [University of Westminster - ISLS] at 13:11 05
December 2013Studies in Higher Education7Data The data for this
study were collected through a questionnaire administered to 425
students in lectures and seminars who were enrolled full-time on
three-year business undergraduate degree programmes at a UK
university during January/February 2009. This means that the nal
year students sampled commenced their university career during the
autumn of 2006 and were among the rst to face a charge of up to
GBP3000 to cover the cost of their tuition. Information was
collected on a students socioeconomic characteristics, their
programme of study, expected debt at the end of their programme of
study, earnings expectations, risk attitudes, and time preference.
After allowance was made for missing values a sample of 308 useable
observations was obtained. The descriptive statistics for the
variables used in the empirical analysis are presented in Table 1.
Column 1 reports the summary statistics for the sample as a whole
and columns 2 and 3 report the sample means and proportions by
gender. We rst note that the proportion of undergraduate students
expecting to be in debt at the end of their time at university is
just over 81%. The full sample of students report an average
expected debt of GBP14,022 and those who anticipate to be in debt
by the end of their undergraduate studies reckon for an average
level of debt of GBP17,276. This latter gure is within the range of
expected debt levels reported for students graduating in 2009
(Purcell and Elias 2010; Push 2010). Although not reported in the
table it is interesting to note that expected debt declines by
cohort. First-year students expect an average debt of GBP14,556 by
the end of their degree programme and the corresponding gures for
second and third/nal year students are GBP14,211 and GBP11,950
respectively. The level of debt reported for third/nal year
students, however, is lower than that reported by Purcell and Elias
(2010). There is a dominance of male students (59%). A large
proportion of the sample are classied as white British (61%) with
14% classied as white non-British and 25% from other ethnic groups
(see notes to Table 1). The sample average age is just over 20,
about 29% hold a part-time job during term time which is lower than
proportions generally reported in national surveys, 85% are from
families that own their own home, and the majority are in their rst
year of study. In terms of student nance about 51% of students
report they are in receipt of a student grant, scholarship or
bursary, and just over 46% receive parental contributions averaging
about GBP152 per month. In terms of future graduate earnings
students expect to earn on average GBP25,108 per annum in their rst
post-graduation job, which is higher than that reported in other
studies (see, Johnson et al. 2009; Purcell and Elias 2010). By the
time the individual reaches the age of 30 they expect to be
earning, on average, GBP50,397 per annum. It is also interesting to
note that for these students they would expect to be earning about
GBP5900 per annum less had they not studied for a degree by the
time they reach 30 years of age. This gure suggests substantial
anticipated returns to their investment in human capital if such
expectations are actually realised. We measure the personal
discount rate by presenting students with ve different scenarios.
In each scenario students were asked to consider if they felt
better off, worse off or the same by comparing a given sum of money
received by a friend in a years time compared to GBP1000 received
by the student today.6 These sums were: GBP950, GBP1000, GBP1050,
GBP1100, GBP1200. The discount factor was elicited on the basis of
when students selected the option the same. Thus, they were
implicitly given one of the following discount factors: -0.05, 0,
0.05, 0.1 or 0.2. The average discount rate was a plausible value
of 0.084. Although simple, this 9. Summary statistics. All students
1Female 2Male 3t-stat/z-scorea/ chi-squared
testb0.8150.7780.8411.4014022.76 (9543.25) 17276.04 (7473.83) 0.591
20.5 (3.195)12499.88 (9460.82) 16236.96 (7432.02) n/a 20.222
(3.091)15077.05 (9482.959) 17934.8 (7449.39) n/a 20.692
(3.258)2.35Ethnicity: White non-Britishc Other ethnic groupd White
British x2 20.139 0.250 0.611 n/a0.183 0.238 0.5790.110 0.258
0.6321.81 0.40 0.93 0.137Cohort: First-year student Second-year
student Third-year student x2 20.623 0.198 0.179 n/a0.667 0.182
0.1510.593 0.209 0.1981.30 0.57 1.06 0.043Proportion of students
expected to be in debt by the end of their studies Students
individual characteristics Expected debt (GBP) all students.
Expected debt (GBP) students who expect to be in debt. Male
students Age (years)1.76 n/a 1.27(Continued .)R. BachanDownloaded
by [University of Westminster - ISLS] at 13:11 05 December
20138Table 1. 10. (Continued .) All students 1Has a
grant/scholarship Has part-time job during term time Students
family characteristics Estimated family annual income (GBP) Father
went to university Mother went to university Receives parental
contribution Monthly parental contribution (GBP) Family home owners
Students future income expectations Expected earnings in rst job
after graduation (GBP) Expected earnings at age 30 with a degree
(GBP) Expected earnings at age 30 without a degree (GBP) Students
attitudes to debt and risk Discount rate Risk attitude Debt
aversionFemale 2Male 3t-stat/z-scorea/ chi-squared testb0.516
0.2920.548 0.2460.494 0.3240.92 1.4853897.73 (36292.16) 0.314 0.256
0.464 152.15 (240.47) 0.85452563.49 (35537.36) 0.349 0.310 0.444
151.49 (227.97) 0.84954821.43 (36874.69) 0.291 0.220 0.478 152.60
(249.37) 0.8570.5425108.77 (8227.349) 50397.73 (22652.85) 44561.69
(44109.64)23821.43 (8119.72) 46190.48 (18447.64) 39984.13
(11131.92)26000.00 (8205.24) 53310.44 (24789.02) 47730.77
(56478.61)0.084 (0.077) 6.166 (2.105) 3.406 (1.289)0.082 (0.077)
5.540 (2.226) 3.810 (1.237)0.086 (0.076) 6.598 (1.906) 3.126
(1.253)1.08 1.97 0.58 0.04 0.19 2.30 2.74 1.52 0.51 4.48
4.739(Continued .)Studies in Higher EducationDownloaded by
[University of Westminster - ISLS] at 13:11 05 December 2013Table
1. 11. R. BachanDownloaded by [University of Westminster - ISLS] at
13:11 05 December 201310Table 1.(Continued .) All students
1Uncertainty aversion N aFemale 2Male 32.990 (1.072) 3082.770
(1.104) 1263.143 (1.025) 182t-stat/z-scorea/ chi-squared testb
3.042t-tests are used to test differences in means between male and
female students, and z-scores are used to test difference in
proportions. The appropriate critical value at 5% level of
signicance is 1.96. b Chi-squared values are used to test the
assumption of independence in the sets of categorical variables
between male and females. The appropriate critical value at the 5%
level of signicance is 5.99. c White non-British includes EU and
other overseas students. d Other ethnic groups include British
Asian, British Afro-Caribbean, British Chinese and other overseas
students. e Standard deviations are reported in parentheses for
continuous variables. 12. Downloaded by [University of Westminster
- ISLS] at 13:11 05 December 2013Studies in Higher
Education11procedure is a standard method of eliciting discount
rates from individuals, has generally found to be a signicant
determinant of student debt (Oosterbeek and van den Broek 2009;
Booij, Leuven, and Oosterbeek 2012), and has been adopted in many
contexts (see, Harrison et al. 2005; Harrison, Lau, and Williams
2002; Meier and Sprenger 2012). Frederick, Loewenstein, and
ODonoghue (2002) provide a critical review of the studies and
techniques used to elicit discount rates since the 1970s. Risk
attitudes were elicited by presenting students with the following
question: How do you see yourself? Are you a person who is fully
prepared to take risks, or do you try to avoid taking risks?
Students were then invited to select a value on an 11-point risk
scale ranging from 0 (not prepared to take risks) to 10 (fully
prepared to take risks). This question has been used to gauge
individual global risk attitudes in the 2004 wave of the German
Socioeconomic Panel (SOEP)7 and has proved to be a reliable
predictor of actual risk-taking behaviour (see Dohmen et al. 2005,
2011; Ding, Hartog, and Sun 2010; Booth and Nolan 2012). The
average for the sample of students is 6.16 suggesting that, on
average, students are prepared to undertake some risky behaviour.
This is broadly similar to that reported by Oosterbeek and van den
Broek (2009). Figure A1a contained in the Appendix depicts the
distribution of risk attitudes across the sample of students. Each
bar represents the percentage of individuals selecting a particular
value on the risk scale. There is some degree of heterogeneity
across the sample. In the extremes a small percentage of students
(1.6%) are not willing to take any risk and have selected zero on
the risk scale, and about 3.6% of students report a high degree of
willingness to take a risk by selecting 10 on the scale. The modal
response is 7, which was selected by just over 26% of students.
Information on student debt aversion was obtained from the question
I am not scared of being in debt. Responses were recorded on a
ve-point scale strongly agree (1), slightly agree (2), neither (3),
slightly disagree (4) and strongly disagree (5). Thus, the higher
the score the more is the students aversion to debt. The mean score
is 3.4 and the median 3 suggesting that on average students are
neutral in respect of their aversion to debt. Similar questions
have been used in previous studies attempting to elicit the degree
to which students are averse to debt (Purcell and Elias 2010;
Oosterbeek and van den Broek 2009). Students were also asked to
indicate their dislike of uncertainty and to indicate their
strength of agreement with the following question: I do not handle
uncertainty well. Responses were recorded on the same ve-point
scale as described above. Thus, the higher the score the better the
student copes with an uncertain situation. The mean score is 2.99
suggesting that students are generally neutral in respect of their
concerns about uncertainty. There are gender differences in the
responses to the questions asked. Relatively fewer females expect
to be in debt by the end of their undergraduate studies compared to
their male counterparts 78% and 84% respectively. Male students
report a higher level of expected debt by the end of their studies
and expect to be more indebted than females by GBP2577 on average.
However, there is no signicant difference between the level of debt
expected between male and females who anticipate being indebted by
the time they complete their studies (t = -1.76). In terms of
ethnicity and age, the female and male sub-samples are broadly
comparable, although white non-British are more represented in the
female than the male sub-samples. In terms of cohort issues, the
majority of females are in their rst year and proportionately more
males are in their second and third years, but these differences
are not statistically signicant at conventional levels. The
sub-samples are also broadly 13. Downloaded by [University of
Westminster - ISLS] at 13:11 05 December 201312R. Bachancomparable
in terms of the proportion of males and females in part-time work,
in receipt of a grant/scholarship and receiving nancial support
from parents. The monthly amount of parental nancial support
received on average is also comparable. Male graduates expect to
earn GBP2179 more than their female counterparts in their rst job
and by the time they are 30 years of age they expect to be earning
GBP7120 more. The nding that males expect higher earnings in their
rst job after graduation is also generally found in previous
surveys (see Purcell and Elias 2010; Johnson et al. 2009). However,
there is no statistically signicant difference between what male
and female students expect to be earning by the time they are 30
years of age had they not studied for a degree. The mean discount
rate reported by males and females is very similar and the
distribution of the discount rate by gender is also broadly
comparable. However there are signicant gender differences in their
reported risk attitudes, their aversion to debt and their dislike
of uncertainty. In terms of risk attitudes females are relatively
less willing to take risks compared to their male counterparts
their scores being 5.54, and 6.59 respectively. Figure A1b in the
Appendix depicts the distribution of risk attitudes by gender. We
rst note that the modal response is 7, which is the same across
gender groups. The gure also reveals that very few male and female
students, approximately 1.6%, report an unwillingness to take
risks. However, at the other end of the distribution, a larger
percentage of males are more willing to take risks than females.
For instance about 60% of males report a risk attitude in the range
of 7 to 10, and 5.5% have selected 10. In contrast about 45% of
female students report a risk attitude in the rage of 7 to 10, and
less than 1% have selected 10. In terms of debt aversion female
students are on average more averse to debt than their male
counterparts, which is a standard nding in the literature. We note
that about 73% of females disagreed with the statement I am not
scared of being in debt with the comparable gure for males about
45%. Similarly, females in the sample appear to dislike uncertainty
more than their male counterparts.Methodology The data employed in
this study can be described as censored. In other words, the
dependent variable, expected debt, records a zero for students who
expect not to be in debt by the end of their studies or a positive
non-zero value otherwise. As a signicant proportion of the sample
of students report zero expected debt, application of OLS to these
data will potentially lead to biased and inconsistent coefcient
estimates. We therefore model student expectation of debt using a
censored tobit model which gives consistent coefcient estimates
when the dependent variable is censored.8 We dene the latent debt
equation as: y = xi b + ui i(1)where y is a partial latent
dependent variable that captures the ith individuals propeni sity
to be in debt, xi is a vector of debt determining variables for
individual i, is a vector of xed unknown coefcients to be
estimated, and ui N(0, 2). Thus: yi = y if xi b + ui . 0 and i yi =
0 if xi b + ui 0 14. Studies in Higher Education13where yi
represents the actual expected debt by the ith individual. Thus yi
is either positive (yi > 0) or zero (yi = 0). Using this
information, the log-likelihood function (L) may be expressed as
follows: nL=Zi lnDownloaded by [University of Westminster - ISLS]
at 13:11 05 December 2013i=1F[(yi x b) 4 s] +(1 Zi ) ln[1 F(x b 4
s)] s(2)where Zi = 1 if yi >0, and Zi = 0 if yi = 0, is the
standard normal density function, is the cumulative distribution
function of the standard normal, and ln() is the natural log
operator. The parameter values , and are chosen to maximise L (the
log-likelihood function) using non-linear iterative methods (e.g.
the Newton-Raphson method). The resultant estimates are known to be
consistent and asymptotically normal. The estimated coefcients are
not readily interpretable as the underlying stochastic index,
expression (1), is not observed when students report zero expected
debt. To aid interpretation the marginal effects for each estimated
coefcient are computed (see Greene 1999). The marginal effects for
the tobit model can be expressed: E[yi |xi ] x i b = bF xi
s(3)Thus, the tobit coefcients have to be adjusted by a factor
equal to (x'i/) to nd the effect on expected debt for small changes
in the independent variables. This scaling factor is constructed in
the current application using the sample average values for xi
variables. Expression (3) can also be used to approximate the
impact effects on expected student debt associated with the
discrete rather than continuous independent variables.Empirical
results Five alternative specications are estimated using a tobit
model, and the corresponding marginal/impact effects are also
estimated for each specication. Each model includes variables that
capture a students individual and socioeconomic characteristics.
The rst specication can be described as an uncertainty model that
includes variables that capture students expected (uncertain)
earnings post-graduation. Specications 2 and 3 augment specication
1 to allow for student discount rates and attitudes to risk to
enter the analysis. Specications 4 and 5 can be described as
behavioural models that augment the uncertainty model to include
students reported debt aversion and dislike of uncertainty (see
Oosterbeek and van den Broek 2009). Table A1 in the Appendix
reports the coefcient estimates for the tobit index functions. We
rst note that the goodness-of-t measures, reported at the bottom of
the Table A1, are satisfactory for models of this kind.
Furthermore, the majority of the estimated coefcients reported in
the table are well determined at a conventional level of
statistical signicance. Each specication was also tested to
determine if separate male and female equations tted the data
better than a single pooled equation using likelihood ratio tests.
The null of a pooled regression was upheld by the data in all
cases. Table 2 reports the estimated maximum likelihood tobit
marginal/impact effects derived from expression (3) for the ve
expected debt equations. Again the majority of the estimated
coefcients, in all ve specications, are well determined at a 15.
Tobit maximum likelihood estimates: marginal/impact effects.
Specication 1Gender (male) White non-British Other ethnic group
White British Age (years) Grant/scholarship Has part-time job
Monthly contribution (GBP) First-year student Second-year student
Third-year student Family home owners Mother and father university
educated Expected earnings >GBP30,000 after
graduationSpecication 2Specication 3Specication 4Specication
52558.898** (1045.40) 2492.986 (1567.60) 4098.849*** (1228.81) f
97.137 (170.55) 1265.626 (1144.21) 8590.715*** (1208.96) 11.709***
(2.56) 1091.396 (1471.92) 4258.316** (1717.30) f 3098.619**
(1420.32) 3281.140** (1381.42) 4050.037*** (1580.87)2490.071**
(1039.27) 2629.599* (1559.04) 4365.615*** (1227.65) f 79.313
(168.93) 1048.938 (1141.36) 8536.019*** (1201.71) 11.628*** (2.55)
1457.336 (1471.88) 4257.002** (1707.18) f 3160.541** (1411.47)
3352.706** (1371.92) 3973.433** (1570.70)1799.670* (1059.86)
2294.468 (1553.61) 3499.635*** (1254.01) f 62.956 (167.92) 753.023
(1135.78) 8441.873*** (1191.73) 11.909*** (2.54) 1565.639 (1459.05)
4430.030*** (1693.76) f 2880.196 ** (1401.89) 3474.237*** (1362.91)
2568.635* (1533.15)2036.378* (1078.06) 2322.105 (1351.12)
3483.319*** (1251.82 ) f 58.074 (167.98) 850.813 (1137.06)
8457.571*** (1189.84) 12.029*** (2.54) 1494.338 (1457.77)
4447.743*** (1689.76) f 2944.440** (1400.45) 3459.429** (1360.58)
2773.774* (1640.40)1589.142 (1068.32) 2219.983 (1549.70) 3313.197**
(1257.58) f 59.870 (167.44) 672.601 (1133.78) 8610.544*** (1194.48)
12.082*** (2.53) 1652.151 (1455.85) 4504.362*** (1689.31) f
3083.756** (1405.45) 3505.761*** (1358.57) 2622.472* (1629.20)
(Continued .)R. BachanDownloaded by [University of Westminster -
ISLS] at 13:11 05 December 201314Table 2. 16. (Continued .)
Specication 1Expected earnings >GBP50,000 at 30 Discount
rateSpecication 2Specication 3Specication 4Specication 52740.183***
(1023.38) 2638.543*** (1008.89) 13628.944** (6441.97) 797.997***
(271.66) 457.355 (400.48) 2711.933*** (1010.96) 13643.780**
(6432.91) 707.777*** (269.71) Risk attitude2745.483*** (1016.79)
14199.556** (6507.81) Debt aversion2590.176*** (1009.78)
13985.731** (6449.61) 750.374*** (268.89) Uncertainty
aversionLog-Likelihood Scale factore Observations a2686.349 0.9209
3082683.987 0.9227 308Asymptotic standard errors are reported in
parentheses beneath coefcient estimates. * denotes signicant at
10%; ** signicant at 5%; *** signicant at 1%. c f denotes base
category in estimation. d denotes variable not used in estimation.
e Scale factor used in the computation of the marginal/impact
effects. f All estimations reported were undertaken using NLOGIT
3.0 (2003). b2680.104 0.9249 3082679.454 0.9255 308635.735 (471.56)
2679.199 0.9258 308Studies in Higher EducationDownloaded by
[University of Westminster - ISLS] at 13:11 05 December 2013Table
2.15 17. Downloaded by [University of Westminster - ISLS] at 13:11
05 December 201316R. Bachanconventional level of statistical
signicance. It should be noted that there is no comparable method
or routine for adjusting the standard errors for the presence of
heteroscedasticity in the tobit model as there is in the OLS
estimated linear regression model (e.g. through use of a robust
estimator). Greene (2008) is critical of the use of such robust
procedures in qualitative response models like the tobit because
the asymptotic properties of such estimates are unknown. He
suggests modelling heteroscedasticity directly, but this is not
feasible in the current application due to the small sample size
available. Moreover, it is not always transparent if such a
procedure actually deals with the problem or merely controls for
some underlying non-linear mis-specication that is unrelated to
heteroscedasticity. We initially focus on a students individual
personal and socioeconomic characteristics and examine their impact
on expected debt. Several of the estimated coefcients relating to a
students individual characteristics are statistically signicant at
conventional levels and the results remain robust across all
specications reported. There is a signicant gender effect on
expected debt. Male students expect to have more debt than their
female counterparts by the end of their undergraduate studies. For
instance, the impact effect in specication 1 suggests that male
students, on average and ceteris paribus, expect a level of debt
that is about GBP2559 greater than that anticipated by female
students at the end of their studies. This effect remains after
controlling for time preference, though the impact diminishes to
GBP1799. However, the estimated gender effect is statistically
insignicant when dislike of uncertainty is included in the
specication possibly suggesting a high intercorrelation between
gender and this uncertainty measure. We nd some evidence that
student ethnicity impacts on expected debt. In the basic
uncertainty model, students classied as being non-white (e.g.
British Asian, black and Chinese) expect to be about GBP4100 less
in debt by the end of their undergraduate studies than their white
counterparts, on average and ceteris paribus. This effect remains
robust across all specications but the magnitude of this effect
diminishes with movement across the ve regression models reported
in Table 2. Students in their second year of study expect a higher
debt than their nal year counterparts, but there is no
statistically signicant difference between debt expectations of
students in their rst and nal years of study. This may be
suggestive of students trying to aggressively reduce their debt in
the nal year of their study. A large and signicant negative effect
on expected debt is found for students who have a part-time job
during term time. The estimated coefcient suggests that holding
such a job reduces expected debt, on average and ceteris paribus,
by about GBP8500 in all specications compared to those students who
are not in part-time employment. This seems to be a plausible
estimate assuming a student earns on average about GBP81 per week
for 35 weeks of the academic year. After some experimentation three
variables that capture the socioeconomic characteristics of the
students family enter the empirical models: parental contributions,
parental educational background and home ownership. First, students
whose parents contribute to their living expenses anticipate their
debt to be reduced by just under GBP12 for every GBP worth of
nancial help received per month according to specication 1. This
represents a rather large multiplier effect and is broadly similar
across all ve empirical specications reported here. Second, on the
basis of specication 1, a student whose mother and father were
university educated expects to be in debt by GBP3281 less than
students with either one or no parent who was university educated,
on average and ceteris paribus. Again this effect remains
reasonably stable across all specications. Third, students from
families that own their own home anticipate to 18. Downloaded by
[University of Westminster - ISLS] at 13:11 05 December 2013Studies
in Higher Education17be about GBP3000 less in debt than students
who do not possess this socioeconomic attribute. There is no
evidence that the age of the student or, rather surprisingly, the
receipt of a grant or scholarship impacts signicantly on expected
debt. However, student expected debt may be inuenced by the
earnings they anticipate in the future, which may also reect a
students expected set of employment opportunities. For instance,
using the results from the rst specication, students who anticipate
earning more than GBP30,000 in their rst post-graduation job expect
to be about GBP4000 more in debt than students who report a more
modest future earnings level. This effect is attenuated as we
control for risk attitudes, aversion to debt and dislike of
uncertainty. A similar, but considerably smaller, effect is found
for those students who expect to earn more than GBP50,000 by the
time they reach 30. In terms of time preference we note that in
specication 2 a one percentage-point increase in the discount rate
increases expected debt by about GBP142.9 A higher discount rate
implies that an individual prefers current consumption to future
consumption and thus we would expect a greater level of expected
debt. The third specication adds the attitude to risk as an
additional covariate. The estimated coefcient is well determined
and statistically signicant and suggests that the less risk averse
the student the higher expected debt.10 Specication 4 introduces
the variable designed to capture the students attitude to debt. The
estimated coefcient is counter-intuitively signed but is
statistically insignificant at a conventional level. Thus, it can
be inferred from this sample that a students attitude to debt
exerts no independent effect on anticipated debt, on average and
ceteris paribus. The nal specication replaces attitude to debt with
an alternative that measures student feelings in regard to
uncertainty. Again the estimated effect for this variable fails to
attain statistical signicance at an acceptable level of statistical
signicance. Conclusion This paper examined the determinants of
student expected debt in UK higher education using a sample of
business and nance students within a single university. We argue
that such an approach using data for a single institution has the
merit of removing the effects of inter-institution heterogeneity.
However, it is acknowledged that some of the results presented may
not be generalisable to the broader UK student population.
Nevertheless, the quality and richness of the data permits the
inclusion of variables that would otherwise be unavailable in
national datasets. We believe that the analysis presented offers
some stylised facts that are likely to be reected in most
comparable UK institutions, and we take the view that the content
of our ndings potentially has broader implications. The results
presented here suggest that there is a gender dimension to student
debt expectations with males having a greater expected level of
debt on the completion of their undergraduate studies than females;
supporting the ndings from the empirical analysis of Purcell and
Elias (2010). This particular result may also reect the role of
greater risk-taking behaviour on the part of male students and
conrms the earlier ndings of Davies and Lea (1995) and Callender
(2003) for pre-university students. Nonwhite students expect a
lower level of debt compared to their white British counterparts.
This may be reective of differing cultural and religious attitudes
to debt (Callender 2003). There also appears to be some change in
the level of debt a student expects 19. Downloaded by [University
of Westminster - ISLS] at 13:11 05 December 201318R. Bachanover
time with second-year students anticipating more in debt than their
rst- and thirdyear counterparts. This could be explained by
changing attitudes to debt over time with students becoming more
tolerant of debt between their rst and second years, but less
tolerant to debt in their nal third year (see Davies and Lea 1995).
Students who work part-time during term time expect to have a lower
level of debt. If there is a trade-off between being a full-time
student and part-time work then raising tuition fees in the future
may compromise the time students will devote to study and may
result in an increase in the non-continuation rate and a reduction
in student academic achievement, particularly among students from
the lower socioeconomic groups. The importance of a students
socioeconomic background as proxied by parental home ownership,
parental experience of higher education and parental nancial
support all were found to exert a signicant role in reducing
student expected debt, and this conrms the ndings of previous
studies (see for example Davies and Lea 1995). In particular, we nd
a sizeable multiplier effect on debt expectations emerging through
parental contributions perhaps suggesting that such contributions
enhances the students sense of nancial security. Whether or not
such contributions are affordable particularly amongst the
lower-income groups merits a close targeting of student support
through the use of bursaries and other forms of student subsidy.
The empirical analysis suggested that the receipt of either a grant
or scholarship or bursary has no signicant effect on reducing
student expected indebtedness. This may be indicative of the fact
that current levels of nancial support are inadequate and
ineffective in reducing anticipated debt and resonates with the
ndings of many recent studies and surveys on student nance and
debt. This issue, and the issues raised above, have clear policy
implications and suggest closer targeting of nancial support to
those students from lower socioeconomic groups, which may
ultimately impact favourably on widening participation in UK higher
education. This is particularly important at a time when the
majority of UK universities are set to increase their tuition fees
to GBP9000 per annum in the academic year 2012/2013. There is
evidence that students anticipate a high return to their university
education in terms of high expected earnings, which in turn
contributes to higher expected debt. Whether or not these
expectations are to be realised in the future is difcult to discern
and may indeed be an overestimate (Jerrim 2011). Moreover, if wage
expectations are unfullled, for instance due to unforeseen shocks
to the graduate labour market or simply because students are
ill-informed on graduate wages and/or job opportunities, then their
life choices could be severely compromised (Jerrim 2011; Callender
and Kemp 2000; Purcell and Elias 2010). Improving the quality of
information on graduate wages and jobs may not only help to match
graduates to jobs but may also help to moderate student wage
expectations and attenuate graduate debt. Finally, we found that
students who have a high discount rate and those with a high-risk
attitude are prone to higher expected debt. This is a novel nding
for UK students and supports the ndings of Oosterbeck and van de
Broek (2009) in their study of the borrowing behaviour of Dutch
students. This study looked at debt expectations of business and
nance students in a single UK university. It would be interesting
to see if these results generalise to other universities and for
students on different degree programmes across the UK higher
education sector. It would also be interesting to see if these
results extend to A-level students contemplating higher education
and whether or not their expectation of debt and the debt they
actually incur in higher education are correlated. These provide
fruitful avenues for further research particularly in the wake of
the 2010 Browne Report. 20. Studies in Higher
Education19Acknowledgments The author would like to thank Barry
Reilly, Mike Barrow, and Yvonne Hillier for constructive comments
on earlier drafts of this paper. The author would also like to
thank the editor of this journal for comments provided and is
particularly indebted to two anonymous referees of this journal for
their constructive and insightful comments. The revised paper has
benetted immensely from their inputs. However, the usual disclaimer
applies.Notes 1.Downloaded by [University of Westminster - ISLS] at
13:11 05 December 20132. 3.4.5. 6.7. 8.9. 10.This commitment was
made in a speech delivered at the Labour Partys conference in 1997.
Parry (2006) discusses the merits and potential pitfalls in moving
from an elite higher education system in the UK to a mass and more
varied higher education system in the1980s and 1990s. It is
instructive to note that participation rates for students under 21
years of age from the lower social classes have increased from
30.6% in 2006/2007 to 39.8% by 2010/2011. Also participation rates
for students from low-participation areas and students from state
schools have also increased between these years from 9% to 10.5%
and 87.4% to 88.7% respectively (Higher Education Statistical
Agency 2012). Evidence from UK national surveys of students income
and expenditure surveys report that the proportion of full-time
students working term time and the hours worked has generally
increased over the last decade, but fell slightly towards the end
of the decade (Callender and Kemp 2000; Callender and Wilkinson
2003; Johnson et al. 2009; Purcell and Elias 2010). The Bank of
England annual spot exchange rates were used to convert the USD
value debt to its sterling equivalent these were 1.5665 for 2009
and 1.546 for 2010. This was undertaken to check for consistency in
responses. For instance, if a student considered GBP1050 received
by the friend the same as GBP1000 today then for lesser amounts
they should feel better off and for greater worse off. Only
students who responded consistently were included in the sample.
Dohmen et al. (2005) provides summary details for the 2004 survey.
The questionnaire is available at
http://www.diw.de/en/diw_02.c.222729.en/questionnaires.html. The
tobit estimator has been used in studies on the determinants of
student loan default (Greene 1989), the determinants of student
part-time work hours (Kalenkoski and Pabilonia 2010), and household
and individual debt expectations (Brown et al. 2005). Amemiya
(1984) provides an early but extensive survey of tobit models.
Given that the discount rate is expressed in proportional terms,
multiplying the coefcient estimate by 0.01 yields the effect of a
one percentage-point rise in the discount factor. In this
specication we test the assumption that risk attitude is exogenous
using the approach suggested by Smith and Blundell (1986). In
conducting this test risk attitude is regressed on a set of four
exogenous identifying dummy variables (instruments) that include
information on whether or not the student: gambles (i.e. regularly
partakes in lotteries); played a fruit machine in the week in which
the questionnaire was administered; had a personal savings account;
and/or ever participated in a dangerous sport. The residuals from
this model are inserted into specication 3 and the statistical
signicance of the estimated coefcient is tested using a t-test.
These variables were found to be individually and jointly signicant
in inuencing risk attitudes with a F(4, 303) = 11.67 [prob-value =
0.000] and the t-test suggests that risk attitude is exogenous
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942793. 24. Studies in Higher EducationDownloaded by [University of
Westminster - ISLS] at 13:11 05 December 2013AppendixFigure
A1a.Student risk attitudes: all students.Figure A1b.Student risk
attitudes by gender.23 25. Tobit maximum likelihood estimates:
index function. Specication 1Gender (male) White non-British Other
ethnic group White British Age (years) Grant/scholarship Has
part-time job Monthly contribution (GBP) First-year student
Second-year student Third-year student Family Home Owners Mother
and father university educated Expected earnings >GBP30,000
after graduationSpecication 2Specication 3Specication 4Specication
52778.829** (1135.057) -2707.252 (1703.659) -4451.135*** (1338.231)
-105.485 (185.223) 1374.403 (1242.840) -9329.065*** (1314.503)
-12.71511*** (2.785663) 1185.199 (1598.316) 4624.307** (1865.06) f
-3364.937** (1542.454) -3563.146** (1502.076) 4398.127**
(1718.200)2698.596** (1126.108) -2849.808* (1691.023) -4731.201***
(1334.493) -85.95528 (183.083) 1136.778 (1237.174) -9250.845***
(1303.963) -12.60206*** (2.772099) 1579.376 (1595.03) 4613.493**
(1850.392) f -3425.212** (1529.731) -3633.47** (1488.673)
4306.177** (1703.67)1945.72* (1145.521) -2480.673 (1680.933)
-3783.644*** (1358.557) -68.06565 (181.5533) 814.1341 (1228.101)
-9126.963*** (1290.228) -12.87514*** (2.754683) 1692.697 (1577.31)
4789.544*** (1831.436) f -3113.935 ** (1515.613) -3756.185**
(1475.511) 2777.089* (1663.05)2200.331* (1164.468) -2509.062
(1677.272) -3763.769 *** (1355.364) -62.74967 (181.5119) 919.3138
(1228.78) -9138.506*** (1287.42) -12.99704*** (2.751435) 1614.65
(1574.97) 4805.839*** (1826.018) f -3181.503** (1513.154)
-3737.955** (1472.095) 2997.096* (1773.093)1716.42 (1153.611)
-2397.787 (1675.025) -3578.558*** (1360.942) -64.66597 (180.8673)
726.4714 (1224.727) -9300.18*** (1291.812) -13.05032*** (2.747557)
1784.475 (1572.276) 4865.126*** (1824.783) f -3330.741** (1517.94)
-3786.544** (1469.363) 2832.511* (1760.28) (Continued .)R.
BachanDownloaded by [University of Westminster - ISLS] at 13:11 05
December 201324Table A1. 26. (Continued .) Specication 1Expected
earnings >GBP50,000 at 30 Discount rate2975.695*** (1112.742)
Specication 2 2975.397*** (1103.299) 15388.66** (7053.512) Risk
attitudeDebt aversionUncertainty aversion9113.382
(425.2541)Goodness of t stats: R2 - ANOVA R2 - Decomposition
Log-Likelihood Likelihood Ratio Test -0.263 0.272 -2686.349 138.95
[0.000]9034.38 (421.4977) 0.275 0.284 -2683.987 143.68
[0.000]Specication 3Specication 4Specication 52800.379***
(1092.935) 15023.42** (6973.531) 811.2701*** (291.0654) 2850.978***
(1091.354) 14726.24** (6961.176) 862.2457*** (293.8944) 494.1774
(432.7096) 2929.138*** (1093.169) 14736.54** (6948.69) 764.4649***
(291.6456) 8923.831 (493.4554) 0.277 0.287 -2680.104 151.44
[0.000]8901.029 (490.5441) 0.281 0.291 -2679.454 152.75
[0.000]686.6526 (509.2374) 8888.974 (492.6188) 0.277 0.290
-2679.199 153.25 [0.000]x2 k(Continued .)Studies in Higher
EducationDownloaded by [University of Westminster - ISLS] at 13:11
05 December 2013Table A1.25 27. R. BachanDownloaded by [University
of Westminster - ISLS] at 13:11 05 December 201326Table
A1.(Continued .) Specication 1Observations a308Specication 2
308Specication 3 308Specication 4 308Specication 5 308All
estimations reported were undertaken using NLOGIT 3.0 (2003).
Asymptotic standard errors are reported in parentheses. c * denotes
signicant at 10%; ** signicant at 5%; *** signicant at 1% d f
denotes base category in estimation. e denotes variable not used in
estimation. f 2 R - ANOVA = variance in predicted conditional mean
over variance in dependent variable. g 2 R Decomposition = variance
in predicted mean over variance in predicted mean plus model
residual variation. h The likelihood ratio test is dened: -2
(Log-likelihood value (constant only) - Log-likelihood value (full
model). The test statistic is a chi-squared statistic with the
degrees of freedom determined by the number of independent
variables (k) in the relevant specication. The null tests the joint
restriction that all the estimated coefcients from a specic
specication are simultaneously equal to zero. b