ContentslistsavailableatSciVerseScienceDirect
The
Social
Science
Journal
jo u rn al h om epa g e :w w w . e l s e v i e r . c o m / l o c a t e/ s o s c i j
Effects
of
soccer
on
stock
markets:
The
return–volatility
relationship
夽,夽夽
M.
Hakan
Berument
a,∗,
Nildag
Basak
Ceylan
baDepartmentofEconomics,BilkentUniversity,06800,Ankara,Turkey
bDepartmentofBankingandFinance,YildirimBeyazitUniversity,06040,Ankara,Turkey
a
r
t
i
c
l
e
i
n
f
o
Articlehistory: Received25March2011
Receivedinrevisedform11March2012 Accepted12March2012
Availableonline16September2012
JELclassification: A12 C22 G12 L83
a
b
s
t
r
a
c
t
Thispaperassessestheeffectsofdomesticsoccerteams’performancesagainstforeign rivalsonstockmarketreturnsaswellasonthereturn–volatilityrelationship.Datafrom Chile,Spain,TurkeyandtheUnitedKingdomsupportpropositionsthatsoccerteamsresults ininternationalcupsaffectstockmarketreturnsandthereturn–volatilityrelationship. EvidencefromSpainandtheUK,soccerpowerhouses,suggeststhatlossesareassociated withlowerreturnsandhigherriskaversionbutevidencefromChileandTurkey,where socceristhemostimportantsportbutteamsarenotassuccessful,revealsthatwinsare associatedwithhigherreturnsandlowerriskaversion.
CrownCopyright©2012PublishedbyElsevierInc.onbehalfofWesternSocialScience Association.Allrightsreserved.
1. Introduction
Afundamentalassumptionofeconomicsisthatagents
arerationalindecisionmaking.Recentliterature,however,
haschallengedthisassumption.Stracca(2004)reviewsa
largebody ofevidence andfinds examplesof irrational
behaviorinnumerousstudies.Behavioraleconomicsand
behavioralfinancetrytoexplainhowemotionsand
cogni-tiveerrorsinfluenceinvestorsandtheirdecision-making
processes. Researchers can explain various stock
mar-ketanomalies,bubblesandcrashesusingpsychologyand
otherrelevantsocialsciencesmethods.Asthepsychology
literature suggests, “mood” is one of the sources of
夽 AlthoughthesportiscalledsoccerinNorthAmerica,itiscalled foot-ballintherestoftheworld.
夽夽 WewouldliketothankthestaffoftheEmbassyoftheTurkish RepublicinSantiago,ConsulateofChileinAnkara,IbrahimKirkayakof theTurkishRadioandTelevisionsportsservice,anonymousreferee,Rana NelsonandOnurIncefortheircontributions.
∗ Correspondingauthor.Tel.:+903122902342;fax:+903122665140. E-mail addresses: berument@bilkent.edu.tr (M.H. Berument),
nbceylan@ybu.edu.tr(N.B.Ceylan).
URL:http://www.bilkent.edu.tr/berument(M.H.Berument).
agent irrationality.FollowingEdmans, Garcia, and Norli
(2007)and Berument,Ceylan, andGozpinar (2006),this
paper claims that mood changes stemming from the
results of soccer matches affect stock market returns.
Thepresentstudyfurtherclaimsthatmoodchangesalso
affect the return–volatility relationship: agents become
morerisk averseafteralossand lessriskaverseaftera
win.
Inthisstudy,wetestwhethermoodhasasignificant
effectonassetprices.Toaccomplishthis,wefirstfindan
eventthatcanaffectthousandsofpeople’smoods
simul-taneously.Sportseventsprovidesuchanexample;soccer
matches in particular. The psychology literature
docu-mentsthatsoccerresultshave amuchlargerimpacton
mood than supposed bymost economistsbecausethey
affectmillionsofpeopleinasimilarway.Somestudies
dis-cusstheeffectof sportsresultsand mood.Forinstance,
Wann,Dolan,Mcgeorge,andAllison(1994)documentthat
fansoftenexperiencestrongpositivereactionsto
watch-ingtheirteamperformwell.Hirt,Erickson,Kennedy,and
Zillmann(1992)findthatIndianaUniversitycollege
stu-dentsestimatetheirownperformancestobesignificantly
betterafterwatchingawinbytheircollegebasketballteam
thanafterwatchingaloss.
0362-3319/$–seefrontmatter.CrownCopyright©2012PublishedbyElsevierInc.onbehalfofWesternSocialScienceAssociation.Allrightsreserved. doi:10.1016/j.soscij.2012.03.003
Mainstreameconomicssupportstheeffectofsocceron
economicperformance.Pollard(2002)documentsthe
rela-tionshipbetweenthegrowthrateofEuropeancountries
andWorldCupsuccess.Moreover,Berument,Inamlik,and
Yucel(2003)andBerumentandYucel(2005)findthat
suc-cessinsocceraffectsindustrialproductioninTurkey.
Similar to the present paper, Edmans et al. (2007),
Berument andYucel (2005) andBerument etal. (2006)
examinetheeffectsofinternationalsoccermatchesona
setofmacroeconomicvariablesviamood.Edmansetal.
(2007)investigatestockmarketreactionstotheoutcome
oftheinternationalsoccermatchesof42countries, and
findthatlossesin internationalsoccermatches havean
economicallyandstatisticallysignificantnegativeeffecton
thatcountry’sstockmarket.However,thesamestudydoes
notfindacorrespondingeffectafterwins:returnsondays
followingwinsareclosetozeroandnotstatistically
sig-nificant.Edmans etal.(2007)suggest thata soccerloss
effectiscausedbyachangeininvestormood.ForTurkey,
Berumentetal.(2006)examinetheeffectsofBesiktas’
suc-cessonstockreturnsandshowthatthisteam’swinsover
foreignrivalsincreasestockmarketreturns.Edmansetal.
(2007)andBerumentetal.(2006)considertheeffectof
lossesandwinsonlyonstockmarketreturns.Incontrast,
ourstudyconsidersnotonlythelevelofreturnbutalsothe
pricingofriskchangeswithsoccerscores.
The existing literature on behavioral finance mostly
concentratesonreturns.However,agents’riskperceptions,
whichthereturn–volatilityrelationshipmaycapture,may
alsochangewithmood.Loewenstein(2000),Romer(2000)
and Loewenstein, Weber, Hsee, and Welch(2001) note
thattheprobabilityweightingfunctionmaydependonan
agent’semotionalstate.Leahy(2002)modelsthe
invest-mentbehaviorofadepressedindividual.Accordingtothat
model,peoplewhoaredepressedbelievethattheyhave
fewpresentandfutureresourcesandbelievetheyhavea
lowutilityofgaininamarketthatisvolatileand
declin-ing.Therefore, depressedindividuals adoptstrategiesto
minimizetheirlosses.JohnsonandTversky(1983)indicate
thatmoodinfluencesjudgmentsofoutcomeprobability.
In one experiment, theyfindthat agents are less likely
togambleafteralossandmorelikelytogambleaftera
gain.Arkes,Herren,andIsen(1988)demonstratethatthe
salesof Ohio’sstate lottery ticketsincrease in thedays
afteravictorybytheOhioStateUniversitysoccerteam.
Similarly,Dohmenetal.(2006)reporttheresultsofa
tele-phone surveyconducted inGermany justone dayafter
theGermansoccerteam’sunexpectedgoodperformance
duringtheFIFA2006WorldCup.Theinterviewswere
re-performedontheafternoonofthenextday.Theauthors
notethatcurrentperceptionandfutureeconomic
expec-tationsimprovedatthepersonalandeconomy-widelevels.
HankeandKirchler(2010)arguethatastheimportance
of amatch increasesand itsresultis moreunexpected,
itsimpactwillbehigher.Edmansetal.(2007)alsonote
thatunderobjectiveprobabilities,marketdeclineisstrong
forunexpectedlosses.Thus,theeffectismorepronounced
afteralossforateamthatismorelikelytowin,i.e.,a
usu-allysuccessfulteam.Theeffectisalsomorepronounced
aftera winfora teamthat isless likelytowin.Tothis
end,wedocumentresultsfromfourcountrieswherethe
soccer is the most important sport. Teams from Spain
and the UK are considered to bemore successfulthan
teamsfromChileandTurkey.Weexpecttoseethatlosses
havelargernegativeeffectsforSpainandtheUKandwe
expectthatwinshavelargerpositiveeffectsforChileand
Turkey.
In this study, we examine the effects of the results
ofinternationalsoccermatchesagainstforeignrivalson
stock exchanges and we report the effect of wins and
lossesoffourcountries’importantsoccerteamsonstock
returns,along withtheireffects onrisk perception.We
organizetherestofthepaperasfollows:Section2
elab-oratesonthemodelthatweuseandSection3provides
the empirical evidence. The last section concludes the
paper.
2. Methodology
In order to assess the effects of soccer matches on
stockmarketreturnsandreturn–volatilityrelationships,
weuseaclassofAutoregressiveConditional
Heteroskedas-tic(ARCH)specifications.TheARCHspecificationcaptures
theconditionalvarianceofstockreturnsasameasureof
risk.
Inthispaper,weuseNelson’s(1991)EGARCH
specifica-tionforconditionalmodelingbecauseofvariousappealing
features.First,itremovespartofthenon-negativity
param-eter restrictions of the conditional variance within the
traditional Bollerslev’s (1986) GARCH model. Second, it
allowsstockmarketshockstohaveasymmetriceffectson
conditionalvariance.Thatis,positiveandnegativeshocks
may affect risk perception differently, i.e., the leverage
effect.
Here,wewanttoseetheeffectsofmoodonrealstock
returns and return–volatility relationships. Our model
specificationis: Rt=xtˇ+ht+·outcomet+ϕ·outcomet·ht+εt (1) εt∼(0,h2t) logh2 t =+ p
i=1 ıilogh2t−i+ q j=1 j εt−j ht−j −Eεt−j ht−j +εt−j ht−j (2)whereRt isthestockreturncalculatedbytakingthe
log-arithmicfirstdifferenceofthedailyclosingpriceofstock
marketsandx
tisavectorforexogenousvariablesattime
t.ThemodelincludesdailydummiesforMonday,Tuesday,
Wednesday,ThursdayandFridaytoaccountforthe
day-of-the-weekeffect.Thexvectoralsoincludeslaggedvaluesof
thereturnbecauseCosimanoandJansen(1988)arguethat
iferrorsareautocorrelated,thenEngle’s(1982)ARCH-LM
testsuggeststhepresenceoftheARCHeffectevenwhenit
isnotpresent.Theconditionalstandard deviationofthe
residualterm,ht,is taken asa proxyfor risk attime t;
outcometisthedummyvariableforthewinsorlossesand
takesthevalueofonefor thenextbusinessdayaftera
winoralossininternationalmatches,andzerootherwise.1
1 Wenotethatwithinthesampleperiodtherewerenevertwoormore
wins(orlosses)tobeconsideredonthenextbusinessday.Therefore, outcometnevertakesthevalueoftwoorabove.
Outcomet·htistheinteractivetermforwinsorloseswith
theconditionalstandarddeviationoftheresidualterm.The
interactivetermisintendedtocapturethechangeinthe
return–volatilityrelationshipwithwinsorlossesandεtis
theerrortermattimet.Asweexpectapositive
relation-shipbetweenwinsandreturns,wealsoexpectanegative
relationshipbetweenlossesandreturns.Thisexpectation
impliesthatthesignoftheestimatedoutcometcoefficient,
,willbepositiveforthewinsofChileandTurkeyand
neg-ativeforthelossesofSpainandtheUK.Ontheotherhand,
thetheoryonchangeinriskaversionsuggeststhatthesign
ofthecoefficientoftheinteractivetermbetweenht and
outcomet,ϕ,willbenegativeforChileandTurkeyand
pos-itiveforSpainandtheUK.Thispredictionisbecausewins
makepeoplelessriskaverse,ormoreriskloving,andlosses
makepeoplemoreriskaverse,orlessriskloving;thuswe
expecttoacceptthesamereturnwithahigherriskora
lowerreturnandalowerriskorahigherreturnwiththe
samerisklevel.
In Eq. (2), the parameter captures residual
asym-metric effects. When =0, a negative surprise, that is,
(εt−1/ht−1)<0, has the same effect on volatility as a
positivesurpriseof equalmagnitude.When−1<<0,a
negativesurpriseincreasesvolatilitymorethanapositive
surprisedoes.When<−1,apositivesurprisedecreases
volatilityandanegativesurpriseincreasesvolatility.
Teamsgenerallyplay alltheirmatchesafterbusiness
hours.MostmatchesareonTuesdays,Wednesdaysand
Thursdays.Therefore,thedummyvariable forwins and
losses,outcomet, forthe nextbusinessdaycan capture
higherreturnsassociatedwiththesedays.However,itis
importanttorecognizedummyvariablesforthe
day-of-the-weekeffect;thus,estimatesforwinsandlossescapture
theeffects ofwinsand lossesaftertheday-of-the-week
effectisaccountedfor.
3. Empiricalevidence
Toassesstheeffectof internationalsoccer scoreson
the stock market, we gather data from four countries
where soccer is an important sports activity;
interna-tionalordomesticsuccessesbelongtoafew teamsthat
havesupportersalloverthecountry.Mostpeople
asso-ciatethemselveswithoneofthefewteams,whichfurther
ensuresthatthesoccerresultswillhaveacountry-wide
effect.Forthesereasons,wechooseChile,Spain,Turkey
and theUK. We select Cobreloa, Colo Colo, Universitad
CatolicaandUniversitaddeChilesoccerteamsforChile;
BarcelonaandRealMadridsoccerteamsforSpain;
Besik-tas,FenerbahceandGalatasaraysoccerteamsforTurkey
and Arsenal, Chelsea, Liverpool and Manchester United
soccer teams for the UK. The time span of the data is
from 01 January 1985 to 02 February 2007, but may
varyamongcountries. Wegatherthedataforthestock
exchangesfromDatastream.Wecomputethestock
mar-ketreturnsbytakingthepercentagechangeofthedaily
closingpriceoftheGeneralStockPriceIndex(IGPA)for
Chile,theMadridStockExchangeGeneralIndexforSpain,
theIstanbulStockExchange100IndexforTurkey,andthe
FTSE100Index fortheUK.We obtaintheinternational
soccermatchresultsforthesefourcountriesmainlyfrom
http://www.rsssf.com.2
Table 1 reports the time period, teams, and
num-ber of international wins, losses, and ties, along with
theirpercentagestototalmatches.Table1suggeststhat
in terms of results, Spain and the UK have more
suc-cessful soccer teams than Chile and Turkey. Because
of the differences in results, we might observe
differ-enteffects oflossesand winsbetweenthetwocountry
sets.
Table2reportsdescriptivestatisticsforthestock
mar-ketreturnsofeachcountry.Notethatexcesskurtosis,the
kurtosisvalueisgreaterthanthree, andthestatistically
significantJarque-BeraTestsfornormalitysuggest
time-varyingvariancesforthereturns.
Table3reportstheestimatesofsoccermatchoutcomest
on stock market returns and return–volatility
relation-ships for the four countries. The estimated coefficients
of outcomet and outcomet·ht are important; however,
we discuss other coefficients to show that our
find-ings parallel the existing literature on the respective
models.
First, the Mondayeffect is negative for allcountries
but Spain,and Tuesday has a negative and statistically
significant effect for Spain.Wednesday alsohas a
neg-ative and statistically significant effect for Spain only.
Thursdays’coefficientsarepositiveforallbutSpain.For
Chile,theThursdayeffectispositiveandstatistically
sig-nificant. Friday effects are positive and are statistically
significantfor Chileat 1%,for Turkeyat5% and forthe
UKat10%significancelevels.Therefore,Mondayreturns
arelowerthanFridayreturnsforallcountriesbutSpain.
However,FridayreturnsarehigherthanTuesdayreturns
for Spain. Thus, our findings are parallel to the
find-ingsintheliteratureontheday-of-the-weekorweekend
effects.
Second,therisktermcoefficient,ht,ispositiveforall
countries. The effectis statisticallysignificantat the1%
significance levelfor Spain,and fortheUKit is
statisti-callysignificantatthe10%significancelevel.Thepositive
coefficientssuggestthatriskincreasesexpectedstock
mar-ket returns.Thisfindingis inlinewiththemainstream
asset-pricing model, which indicates the association of
higherreturnswithriskierportfolios.
Third,consistentwiththeexistingliterature,outcomet
coefficientsarenegativewhentheSpanishandBritish
soc-certeamsloseandpositivewhentheChileanandTurkish
soccer teamswin. Thisfindingsupports theproposition
thathighermoraleincreasesstockmarketreturnsforthe
cases of wins and decreasesreturns after a loss. These
resultsmakesensebecauseSpainandtheUKare
success-fulcountriesinsoccer.Thus,winsmaynotaffectthemood
ofsoccerfansasmuchaslosses.Forthisreason,weexpect
theeffectsoflossestobehigherforthosecountries.Onthe
otherhand,ChileandTurkeyarenotassuccessfulinsoccer
asSpainandtheUK.Thus,winsaremorelikelythanlosses
2Wealsousehttp://www.statto.com/,http://kassiesa.home.xs4all.nl/ bert/uefa/data/index.html and http://www.eurocupshistory.com/uefa cup/tofindorvalidatesomeofthematchresults.
Table1
Thenumberofwins,tiesandlossesforeachcountry.
Sampleperiod Numberscoreson
Wins Ties Losses
Chile 02January1987–31December2006 94 73 90
(37%) (28%) (35%) Cobreloa 22 18 26 (33%) (27%) (40%) ColoColo 31 22 25 (40%) (28%) (32%) UniversitadCatolica 30 24 25 (38%) (30%) (32%) UniversitaddeChile 11 9 14
Spain 01November1977–02February2007 298 112 127
(55%) (21%) (24%)
Barcelona 151 62 60
(55%) (23%) (22%)
RealMadrid 147 50 67
(56%) (19%) (25%)
Turkey 03July1987–02February2007 99 65 109
(36%) (24%) (40%) Besiktas 27 19 30 (36%) (25%) (39%) Fenerbahce 24 11 35 (34%) (16%) (50%) Galatasaray 48 35 44 (38%) (28%) (34%)
UnitedKingdom 01January1985–02February2007 249 120 107
(52%) (25%) (23%) Arsenal 59 33 31 (48%) (27%) (25%) Chelsea 47 17 20 (56%) (20%) (24%) Liverpool 63 29 25 (54%) (25%) (21%) ManchesterUnited 80 41 31 (53%) (27%) (20%)
Source:Thedataonthesoccerscoresarefromhttp://www.rsssf.com.
Numbersinparenthesesarethepercentagesofthecorrespondingoutcomes(wins,tiesorlosses)tototalmatches.
toaffectthestockmarketreturnandthereturn–volatility
relationship.
Finally,weconsidertheinteractiveterm,outcomet·ht.
ThecoefficientsarenegativeforChileandTurkeyand
posi-tiveforSpainandtheUK.ThenegativecoefficientsforChile
andTurkeysuggestthatmarketscompensateagentsless
afterawinforbearingthesamelevelofrisk;thatis,agents
aremorerisklovingafterawin.Thepositivecoefficientsfor
SpainandtheUKsuggestthatmarketscompensateagents
moreafteralossforbearingthesamelevelofrisk;agents
becomemoreriskaverse.Weestimatethesame
specifica-tionsforSpain’sandtheUK’swinsandChile’sandTurkey’s
losses.Wedonotreporttheseestimatesheretosavespace
buttheyareavailablefromtheauthorsuponrequest.
Nei-therthe outcome coefficients northe interactiveterms
are statistically significant, supporting the proposition
Table2
Descriptivestatisticsofthecountries’stockmarketreturnsintherespectivesampleperiods.
Chile Spain Turkey UnitedKingdom
Mean 0.075580 0.050450 0.217808 0.032523
Standarddeviation 0.842854 1.057097 2.987632 1.006494
Skewness −0.258825 −0.118161 0.180407 −0.586982
Kurtosis 11.659901 5.622417 3.028642 9.673965
Jarque-Bera 29457.843566 10020.099049 1837.702786 22676.560464
Source:DataforthestockexchangesarefromDatastream.
Notes:Returnsarecalculatedbytakingthepercentagechangeofthedailyclosingpriceofthestockexchangeindexes.WeusedtheGeneralStockPrice Index(IGPA)forChile,theMadridStockExchangeGeneralIndexforSpain,theIstanbulStockExchange100IndexforTurkey,andtheFinancialTimesStock Exchange100IndexfortheUK.
Table3
Effectsofsoccermatchoutcomesonstockreturnsandthereturn–volatilityrelationship.†
Outcome– losses Outcome–wins
Spain UK Chile Turkey
PanelA:estimatesforthereturnequation
Monday 0.0390* −0.0145 −0.1268*** −0.1728 (0.0761) (0.6509) (0.0000) (0.1122) Tuesday −0.0814*** 0.0303 0.0092 −0.1428 (0.0000) (0.4433) (0.7355) (0.1997) Wednesday −0.0485* 0.0425 0.0290 0.0744 (0.0643) (0.1824) (0.2944) (0.5199) Thursday −0.0107 0.0223 0.0671** 0.0774 (0.6087) (0.4859) (0.0155) (0.4917) Friday 0.0224 0.0732* 0.0782*** 0.2383** (0.5070) (0.05384) (0.0051) (0.0370) Outcomet −0.1298** −0.5265*** 0.3110** 1.2969** (0.0306) (0.0007) (0.0421) (0.0423) ht 0.0438*** 0.0139* 0.0246 0.0457 (0.0000) (0.0815) (0.5294) (0.2550) Outcomet·ht 0.0969* 0.6350*** −0.6318** −0.6102** (0.0571) (0.0002) (0.0233) (0.0330) PanelB:estimatesfortheEGARCHspecifications
Parameters K 0.0102*** −0.0048 −0.0212** 0.1027*** (0.0051) (0.2605) (0.0120) (0.0000) logh2 t−1 0.9893*** 0.1230*** 0.5426*** 1.0198*** (0.0000) (0.0000) (0.0000) (0.0000) logh2 t−2 0.8470*** 0.4028*** −0.3890** (0.0000) (0.0000) (0.0148) logh2 t−3 0.3224*** (0.0002)
εt−1 ht−1−E εt−1 ht−1+ εt−1 ht−1 0.3015*** 0.1477*** 0.4011*** 0.3638*** (0.0000) (0.0000) (0.0000) (0.0000) εt−2 ht−2−E εt−2 ht−2+ εt−2 ht−2 −0.0746** 0.1237*** (0.0204) (0.0000) εt−3 ht−3−E εt−3 ht−3+ εt−3 ht−3 −0.0510* −0.0200 (0.0752) (0.4829) −0.0939** −0.3877*** 0.0211 −0.0764** (0.0152) (0.0000) (0.5730) (0.0387) TT 4.8537*** 11.1588*** 5.6742*** 7.4441*** (0.0000) (0.0000) (0.0000) (0.0000) Functionvalue −5155.5998 −3952.5773 −2176.8415 −8510.7244 PanelC:Ljung-BoxQ-statisticsLags
5 0.1118 0.5300 0.0297** 0.0195**
10 0.3229 0.9171 0.1784 0.1531
20 0.0859* 0.8559 0.1642 0.5242
60 0.4049 0.8722 0.2672 0.8138
PanelD:ARCH-LMtests Lags
5 0.9974 0.0016*** 0.0383** 0.4072
10 1.0000 0.0331** 0.1909 0.0152**
20 1.0000 0.1747 0.5037 0.0584*
60 1.0000 0.8863 0.4444 0.2204
PanelE:non-parametric(sign)tests
Signbiastest 0.3570 0.7859 0.0298** 0.3159
Negativesizebiastest 0.4256 0.2170 0.4949 0.4659 Positivesizebiastest 0.4521 0.2515 0.0812* 0.3155
Jointtest 0.3625 0.3856 0.1546 0.3595
Source:Thedataonsoccerscoresarefromhttp://www.rsssf.comandthedataonreturnsfromDatastream.
† Wereportp-valuesinparentheses.Theestimatedcoefficientsforthelaggedvaluesofthedependentvariableshavenotbeenreportedtosavespace.
***Indicatesthelevelofsignificanceatthe1%level. ** Indicatesthelevelofsignificanceatthe5%level. * Indicatesthelevelofsignificanceatthe10%level.
that losses have more of an effect on the countries
withmoresuccessfulsoccerteams;however,winshave
more of an effect on countries with less successful
teams.
The estimates for the EGARCH model and a
bat-tery of specification tests for the model are reported
in Table 3’s Panels B–E. We show the estimated
the countries under consideration, the coefficients of
log(ht−i)2 and
εt−j/ht−j−Eεt−j/ht−j+εt−j/ht−j aresignificantlydifferentfromzero.3 Thelagged-value
esti-matedcoefficientsoflog(h2
t)arestatisticallysignificantand
thecharacteristicrootsofthepolynomialareallinsidethe
unitcircle.Thus,noneoftheconditionalvariance
specifi-cationsisexplosive.Evidenceontheleverageeffect,the
estimated coefficientfor theleverage effect,, is
nega-tiveforSpain,TurkeyandtheUK,indicatingthatnegative
surprisesincreasevolatilitymorethanpositivesurprises.
However,wedonotobserveastatisticallysignificant
lever-ageeffectforChile.
TosetupthemaximumlikelihoodestimatorforEqs.
(1)and (2),weassumethaterrors haveaGeneralError
Distribution.TTistheparameterforreturntailthickness.
ATT>2impliesthaterrorshaveathickerdistributionthan
normal.
Panel C reports the p-values of the Ljung-Box
Q-statistics forthestandardized squaredresiduals, (ε2
t/h2t),
calculatedtotestthenullhypothesisofzero
autocorrela-tionupto60lags.Overall,wecannotrejectthenullofno
autocorrelationforanycountry.Theonlyexceptionsare
Spainat20lagswithasignificancelevelat10%,andChile
andTurkeyatfivelagswithasignificancelevelat5%.
Next, totestfor thenull hypothesisthat there isno
ARCHeffectforthestandardizedresiduals(εt/ht),weapply
Engle’s(1982)ARCH-LMtest.Teststatisticsforthe
stan-dardizedresidualsarereportedinPanelC.Totestthenull
hypothesisthatthereisnoARCHeffect,weregressedthe
squaredstandardizedresidualsonaconstanttermandon
itsfifth,tenth,twentiethandsixtiethlags.Here,theaimis
totestwhetherlagtermsarejointlystatisticallysignificant;
theresultsshowthatthenullofnoARCHeffectisrejected
onlyforChileatfivelagsatthe5%significancelevel,for
Turkeyat10lagsatthe5%significanceleveland20lagsat
the10%significancelevelandfortheUKatfiveand10lags
atthe1%and5%significancelevels,respectively.
PanelEreportsthenon-parametricsignandsizebias
testsperformedforthestandardizedresiduals(εt/ht).
Cal-culatingtheteststatistics,weusestandardizedresiduals
(εt/ht).We addtwo dummyvariables,mt andpt,tothe
equationsuchthatmt=1ifthenormalizedresidualis
neg-ative,0otherwise,andpt=1ifitispositive,0otherwise.
Wealsodefinetwointeractivedummyvariables:smtand
spt.
smt=pt∗(εt/ht) and spt=pt∗(εt/ht)
smt=pt·(εt/ht) and spt=pt·(εt/ht)
Later,weregress(εt/ht)ontheconstantterm,mt,smtand
spt.Inthesigntest,wedeterminewhetherthecoefficient
ofmiszeroornot.Withthenegativesigntest,we test
whetherthecoefficientofsmt iszero;withthepositive
signtestwetestwhetherthecoefficientofspiszeroand
withthejointtestwetestthesenullhypothesesjointly.
3Wedeterminetheselectionofthelagorderforbothtermssuchthat
thespecificationtestsreportedinPanelsB,C,DandEdonotrevealthat standardizedresidualsarenotiid.
Theresultsshowthatnocountry’steststatisticsare
statisti-callysignificant,exceptforthesignbiasedtestandpositive
sizebiastestforChile,whicharestatisticallysignificantat
the5%and10%levels,respectively.Hence,sincemosttest
statisticsreportedinPanelsB–Earenotstatistically
signif-icant,weconcludethattheysupportourspecifications.
4. Conclusions
This paper presents empirical evidence that soccer
matchscoresaffectstockmarketreturnsandstockmarket
return–volatility relationships. Evidence from countries
withrelativelymoresuccessfulsoccer teams,Spainand
theUK,indicate stockmarket returnsdecrease and the
risk–returnrelationshipchangeswiththematchscoreso
thatagentsbecomemoreriskaverseafteraloss.However,
we cannotfind statisticallysignificantevidencefor this
changeafterawin.Thedatafromcountrieswithrelatively
lesssuccessfulsoccerteams,ChileandTurkey,revealthat
stockmarketreturnsincreaseandagentsbecomemorerisk
lovingafterawin.Similarly,wecannotfindstatistical
sig-nificanceafterlosses.Themore-pronouncedlosseffectfor
SpainandtheUKandwineffectforChileandTurkeymaybe
duetosuccessfulhistoriesorfanexpectationsfromthese
countries’soccerteams.
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