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7
ADOPTION OF TECHNOLOGIES UITH NETWORK
EFFECTS:
An
Empirical Examination
of theAdoption of Automated Teller Machines
Garth Saloner
and
Andrea Shepard
No. 577April 1991
massachusetts
institute
of
technology
50 memorial
drive
Cambridge,
mass.
02139
ADOPTION
OFTECHNOLOGIES
WITH
NETWORK
EFFECTS:
An Empirical
Examination
of theAdoption of Automated Teller Machines
Garth Saloner
and
Andrea Shepard
JUL
1 8 1991 RfeO.*ADOPTION
OF
TECHNOLOGIES
WITH
NETWORK
EFFECTS:
An
Empirical
Examination
of
the
Adoption
of
Automated
Teller
Machines*
Garth
SalonerStanford University
and
Andrea
Shepard
Massachusetts
Institute ofTechnology
Current Version: April 9, 1991
ABSTRACT
The
literatureon
networks
suggests that thevalue ofanetwork
is positively affectedby
thenumber
ofgeographically dispersed locations it serves (the"network
effect")and
thenumber
ofitsusers (the "production scale effect").We
show
that as aresulta firm's
expected time
untiladoption
of technologieswith
network
effects declinesin
both
usersand
locations.We
provide empirical evidenceon
theadoption
ofautomated
tellermachines by banks
that is consistentwith
this prediction.Using
standard
duration models,we
find that a bank's date ofadoption
is decreasing inthe
number
ofitsbranches
(aproxy
for thenumber
of locationsand
hence
for thenetwork
effect)and
the value ofits deposits (aproxy
fornumber
ofusersand
hence
for
production
scale economies).The
network
effect is the larger ofthetwo
effects.*
We
would
like tothank
Timothy
Hannan
and
John
McDowell
for generouslyallowing us to use their data,
Stephen
Rhoades
and
Lynn
Flynn
at theBoard
ofGovernors
for providing Federal Reserve data,Keith
Head
and
Christopher
Snyder
for research assistance,
Robert Gibbons,
Nancy
Rose,and
JulioRotemberg
forseveral helpful discussions,
workshop
participants atHarvard
and
theNBER
foruseful
comments,
the National ScienceFoundation (Grant
IST-8510162), theSloan
Foundation,
and
theTelecommunication
Businessand Economics
Program
atMIT
forfinancial support.1.
Introduction
With
the proliferation of information technology over the past several decades,net-works have
become
increasingly important.Examples
include banks'automated
teller machines, airlines'
customer
reservation systems,and
thegrowing
network
of facsimile machines. In such networks, the value to each individual orfirm ofpartic-ipating increases
with
network
size.Network
effects,and
demand-side economies
of scalemore
generally,have been
shown
in theory tohave
implications for a variety ofimportant
economic
activities including technology adoption, predatory pricing,and
product
preannouncements.
1There have
not, however,been
any attempts
totest econometrically for the effects of
networks
on
thesephenomena.
2In this
pa-per
we
constructand
apply a test fornetwork
effectson
theadoption
by banks
ofautomated
tellermachines
(ATMs).
For telephone systems,
which
areperhaps
the bestknown
example
ofatechnol-ogy with important network
effects, there aretwo
types ofeffects. First, the benefit of the technology toan
individual user increases in thenumber
of telephones, i.e.,in the
number
oflocationsfrom which
thesystem can be
accessed.This
size effectalso exists, for
example,
in retail distributionnetworks
where
consumer
benefitin-creases in the
number
of outlets atwhich
thegood
is available. Second, the benefit increases in thenumber
of peoplewho
areon
the system: as thenumber
of peoplewho
make
and
receive calls increases, each individualcan
communicate
with
more
people.
This second
effect is the source ofnetwork
externalitiesbecause
each
new
user confers
a
benefiton
all other users.In the case of
ATMs
thenetwork
effect is of the first type.A
cardholder isbetter off the larger the
number
ofgeographically dispersedATMs
from
which
shecan
access her account.The
convenience of access to one's accountwherever one
happens
tobe
means
that the value of theATM
network
increases in thenumber
ofATM
locations it includes.A
bank
can
increase itsnetwork
sizeby
adding
more
ATMs
to its proprietarysystem
and
by
linking itsnetwork with
thenetworks
of1
See, for
example,
Katz and
Shapiro (1986)and
Farrelland
Saloner (1985,1986).2
Several case studies
have
been conducted
to confirm the relevance of the the-ories.For example,
David
(1985) argues thatdemand-side economies
explain theother banks. In the early days of
ATM
adoption studied here, interbanknetworks
were
quite rare for a variety of technicaland
institutional reasons.As
a result the value of thenetwork
to depositorswas
increasing in thenumber
ofATM
locationsin their bank's network.
Because
differences in banks' post-adoptionnetwork
sizewould
generatedif-ferent valuations to their depositors, the value of
adopting
an
ATM
system
would
be
higher forbanks
expecting tohave
larger proprietarynetworks
in equilibrium,all else equal.
Because
new
technologies diffuse graduallythrough
an
industry, itis
common
and
reasonable to expect those firms that value the technologymore
toadopt
earlier. Ifeither thecost ofadoptingan
ATM
network
ofa given size fallsovertime
(becausebanks and/or
suppliershave
alearningcurve) or the benefit rises overtime
(because depositors learnabout
the value ofATMs
orATMs
perform
more
functions),then
banks with
a relatively higher valuation of the technology atany
point intime
willadopt
relatively early.A
reasonable version ofthenetwork
effects hypothesis, therefore, is thatbanks
expecting to
have
a largernumber
of locations in equilibrium willadopt
sooner.To
test this hypothesis
we
proxy
unobservableexpected
network
sizeby
thenumber
ofbranches
abank
has.Branches
are agood
proxy
forexpected network
sizebecause
they
are themost
common
location forATMs,
they are the lowest-cost locations,and
because
legal restrictions limitedplacement
outsidebranches
during thesample
period. Further,
commentary
in the trade pressand
casualempiricism
suggest thatbanks
eventually placeATMS
in most, if not all, branches.Accordingly
we
focuson
the likelihood thatbanks adopt
as a function of thenumber
ofbranches
theyhave.
The
net value ofan
ATM
system
to abank
also willbe
affectedby
thenumber
of its depositors towhom
ATMs
are valuable.Because
there are fixed costs ofadoption,
economies
of scale in productionmean
that a bank's propensity toadopt
will increase in the
number
of these depositors. Indeed, earlier studies ofATM
adoption
by
Hannan
and McDowell
(1984, 1987) find thatbank
size, asmeasured
by
total assets, isan important determinant
oftime
of adoption.We
confirm
these results
by
including ameasure
of sizemore
directly related to thenumber
ofwe
are able to separate thenetwork
effectfrom
the scaleeconomies
effect.Controlling for variation in the
number
of depositorsand
other heterogeneity,we
find that increasingnetwork
size increases the probability of early adoption.When
evaluated at thesample
mean,
the estimated probability that abank would
have adopted
in the first nine yearsATMs
were
available is 17.1 percent.Adding
a single
branch
increases this probabilityby
at least 5.7 percent (to 18.1 percent)and
perhaps
by
asmuch
as 10 percent. In comparison,adding
enough
depositorsto equal
an
average sizedbranch
increases the adoption probabilityby
4.3 percent.The
strongnetwork
effect is robust to specificationand
toremoving
large outliers.In section 2,
we
discuss the determinants ofATM
adoptionand
develop a test fornetwork
effects. In Section 3we
briefly discuss the statisticalmodels
used.The
data used
toimplement
thesemodels
are discussed in Section 4,and
in Section 5we
presentour
results. Section 6 providessome
concludingcomments.
2.
Network
Effects
and
ATM
Adoption
In this section
we
develop aframework
for considering a bank'sadoption
decision.While
thisdiscussion does not identifystructuralparameters, it does provideinsight into the relationshipbetween network
sizeand
a bank's propensity toadopt
ATMs
that guides the empirical analysis. In particular,
we
focuson
distinguishing theeffect of
network
sizefrom
the effect ofthenumber
ofend-users.In our context, end-users are the bank's depositors
and
the relevantmeasure
of
network
size is thenumber
of physical locations atwhich any
given depositorcan
carry outa
transaction.While
each user is largely unaffectedby
thenumber
ofother users of the
same
network, each user is better off the greater thenumber
of outletsfrom
which
shecan
access the network. Feasible locations forATMs
include the bank'sbranches
and
may
also includesome
non-branch
locations.3To
simplifytheanalysis
and
be
consistent with thedata
availableforempirical work,we
assume
that if a
bank
decides toadopt
ATMs
it willbe
optimal for it to installATMs
inall feasible locations
and
make
thesystem
accessible to all its depositors.3
As
discussedin asubsequent section,placingATMs
outsideof existingbranches
We
startwith
banks
endowed
with a set of characteristics including itsdepos-itors
and
feasibleATM
locations.Throughout
the analysis,we
treat thesecharac-teristics as predetermined, focusing
on
the adoption decision conditionalon
bank
characteristics.
With
thenumber
of depositorsand
potentialnetwork
size prede-termined, abank
decideswhether
toadopt
an
ATM
system
ofa fixed size to servea fixed
number
of depositors and, if so,when.
The
bank's decision,depends
on
the flow of benefitsand
costsfrom
adoption.We
begin
by
considering the "benefit side",and
in particular, the benefits toan
individual user. In the theoretical literature
on network
effects,an
end-user's per period benefits are frequently representedby
a+
b(N),where
a represents the "stand-alone" benefitfrom
the technologyand
b(N)
represents thenetwork
effect.4The
"stand-alone" or"network
independent"component
ofthe user's benefit is thatwhich
the user obtains regardless ofthe sizeofthe network.Thus,
amight
representthe utilitythat a depositor receives
from
havingan
ATM
installed at thebranch
she"usually" uses: the depositor
may
get superior service simplyby
substituting theautomated
teller for thehuman
one
duringnormal
business hours,and
willbe
able to lengthen the period duringwhich
shecan
transact at thatbranch
by
substitutingan
after-hoursATM
for adaytime
teller.The
network
effect term, b(N), increases inN
which measures
the size of thenetwork
(JV>
1).The
variableN
then represents thenumber
of other locationsfrom
which
a depositoris able to accessher accountfrom
an
ATM.
IfthoseATMs
arelocated at existing
branches
the benefits they provide are oftwo
kinds. First, they provide the benefits discussedabove
of substitutingmachines
for tellersand
after-hours
use fordaytime
use. Second,by
standardizing depositor identificationand
account
access procedures the existence ofan
ATM
inbranches
otherthan
theone
at
which
the user hasan
accountmay
make
it easier for the userto transact at those branches. IftheATMs
are not locatedat existingbranches, theyeffectively increasethe
number
ofbranches
(for the subset oftransactions thatcan
be performed by an
ATM).
54
See Farrell
and
Saloner (1986) for example.5
In this setting a
probably
depends
on
N.
The
valueofhaving
an
ATM
at one'sThe
aggregate per period value of theATM
network
to a bank's depositors ifthere are
n
ofthem
is n[a+
b(N)]. In generalone
might
expect the per periodbenefits to increase with calendar time as the
number
of serviceswhich
ATMs
provide increase. In
what
followswe
suppose
that benefitshave
growth
factor g,where
g>
1.The
flow of benefits that the bank's users derivefrom an
ATM
during
period t is therefore [a
+
^N^g*.
Assuming
that the per-period increasein revenuesto the
bank
is proportionalto theper-period benefitsto the depositors (inparticular if the bank's revenues are A times the benefit to depositorswhere
A<
1),then
thepresent value of the bank's revenues (evaluated at time
T) from adopting an
ATM
at
time
T
are:oo
J]An[a
+
6(iV)]^
T+t (1)<=o
where
8 is the discount factor.Note
that these benefits are increasing inboth n
and
N.
6We
turnnow
to the "cost" side ofthe analysis. Inmaking
itsadoption
decision,the
bank must
considerboth
variableand
fixed costs.The
variable costs aremainly
supplies (such as film) that are incurred with each transaction.
Because
we
assume
that each depositor
makes
thesame
number
of transactions, the variable costs are proportional to thenumber
of depositors. For simplicity,we assume
that thevariable costs are incorporated in A so that \n[a
+
b(N)]glrepresents the benefit
net of variable cost in period < to a
bank
that hasadopted
an
ATM.
The
fixed costs include the cost ofmaking
alterations tobranches
toaccom-modate
ATMs,
expenses related to adapting the bank'scomputer
software to theATMs,
the cost of purchasing or leasing theATMs
themselves, the cost of service tomaintain
the distinctionbetween
stand-alone effectsand
thenetwork
effect ofadditional locations in
what
follows. For simplicitywe
suppress thedependence
ofa
on
N
in the notation. If this effect isimportant
it will reduce thenetwork
effectmeasured
in the empirical work.6 For reasons discussed
at length later (principally that
banks
did not shareATM
networks
in the 1970s),we
assume
thatbank
A's depositors areunable
to usebank
B'sATMs.
ThereforeN
represents only the bank'sown
ATM
locations. Ifsuch networks were
sharedand
if abank
thereby obtainedsome
benefitsfrom
theadoption
ofATMs
by
other banks, theremight
be
an
externality in banks'adoption
decisions. In
our
case,where
each bank'snetwork
benefits areindependent
ofother banks' actions,no
externality is involved.Hence
theterm "network
effect".and
the cost of marketing.Many
of these costs, such as the cost ofpurchasing
or leasing
ATMs
or of installingthem,
depend
on
N.
Others, such as software ormarketing
costs, are"system
costs"and
are arguablyindependent
ofN.
We
de-note the present value of the cost of adopting
an
ATM
system
inN
locations attime
T
asC(N,T)
=
S(T)
+
JVc(T),where S(T)
represents thesystem
costsand
c(T) represents the cost per location.
A
typicalassumption
in the literatureon
the
adoption
of technology,and
one which
we
make
as well, is that the fixed cost ofadopting
the technology,C(N,T),
declines overtime
as the suppliers'and/or
the banks' experience
with
the technology accumulates.The
net present value ofa
bank's profitsfrom adopting
ATMs
at timeT
is therefore:oo
II
=
^
A«[a+
b(N)]6tgT+t-
C(N,
T).<=o
A
bank
with
n
depositorsand
N
locations earns higher profitsfrom adopting
at
time
T
than
from
waiting until timeT +
1 if:A*
T
f
+
«*>'
-C(N,T)
>
if**'*
1*?
KN)]
-
C(N,T
+
1)), 1—
og V 1—
Og tAnto
+
W-^,,^
1-
og i.e., if Xn[a+
b(N)]gT
> C(N,T) - 6C(N,T
+
1). (2)The
assumptions
that variable profitsgrow and
the cost ofadoption
declines overtime
implies that everybank
eventually finds it profitable toadopt
ATMs.
This
allows us to focus
on
when,
ratherthan
whether,adoption
takes place.Provided
the rate of decline of the cost of
adopting
decreases over time, the smallestT
thatsatisfies
Equation
(2) is the optimal time to adopt.7There
aretwo
interesting polar cases ofEquation
(2).The
first iswhere
C(N,
T)
is constant overtime
so thatgrowth
is the only factor in thetiming
ofadoption. In that case
Equation
(2) reduces to:Xn[a
+
b(N)]gT
1-8
>
C(N),
7
A
similarmodel
of the optimaladoption
time (butwithout
network
effects) isi.e., the
bank
adopts assoon
as the net present value of variable profitsassuming
no
further
growth
exceeds the cost ofadoption. Since costsdo
not declinewith time
in this case there isno
point to waiting: future per-period profits willbe
higherthan
today's,
and
ifadoption
would be
profitable with astream
of profits equal to thisperiod's, the
bank
should adopt.The
second
polarcaseiswhere
thereisno growth
(g=
1)and
theonlytemporal
effect is the declining cost of adoption over time.Then
Equation
(2)becomes
\n[a
+
b(N)]> C(N,T) - SC(N,T
+
1).The
right-hand-side ofthis expression isthe cost-saving
from
delaying adoptionby one
period,and
thebank
adopts
assoon
as that cost saving is less
than
the (constant) per-period variable profit.The
general case(Equation
(2)) is acombination
of thesetwo
effects.The
bank
adoptswhen
the per-period variable profits exceed the cost-saving ofwaitingan
additional period.Each
period adoptionbecomes
more
tempting both because
per-period variable profits are higher
and
because the cost ofadoption
is lower. In thismodel
n
enterson
the left-hand-side of (2) only, i.e., it increases thebenefits (net of variable costs)
and
does not affect fixed costs.As
isapparent
by
dividing (2)
by
n, the bank's net benefit per depositor is constant, but total costsdecline in n; there are production side
economies
of scale inATM
systems.As
aresult of these scale economies, the bank's profit
from an
ATM
system
is increasing in n. Therefore,adoption
occurs earlier the larger thenumber
of depositors.In the empirical work,
we
are interested primarily in testing for anetwork
effect
and
assessing itsmagnitude.
This requires separating the effect of variationin
network
sizefrom
the effect ofvariation innumber
ofdepositors.One
simple testfor
network
effects is to estimate the effect of variation inN
holdingn
constant.However
correctly interpreting the result is complicatedby
the cost-side effects.The
overall effect ofN
on
the timing of adoption isambiguous
since it affectsboth
the left-and
right-hand-sides of (2).The
left-hand-side of (2) is increasingin
N
because
of thenetwork
effect.However,
the right-hand-side also increases8
The
assumption
that fixed costs are nota
function ofn
is violatedifusage
levelsvary across locations, particularly if
banks respond
to usage variationby
varyingthe
number
ofATMs
across locations. MultipleATMs
per locationwas
perhaps
less
common
in the early days ofATM
adoption studied herethan
it isnow.
Iffixed costs increase in n, the sign of the overall effect ofn
is, in principle,ambiguous.
with
N.
To
see this recall thatC(N,T)
=
S(T)
+
Nc(T),
so that theright-hand-side of (2) is [S(T)
-
S(T
+
1)]+
N[c(T)
-
c(T
+
1)].Two
banks with
differentnumbers
of locations enjoy thesame
benefits in terms of reduction in thesystem
costs if they wait;
however
thebank
withmore
locations reaps the reduction inthe location specific costs at
more
locations.Thus,
holdingn
constant,banks with
more
locations willadopt
earlieronly ifthenetwork
effectoutweighs
this cost effect.Consequently a
test thatmeasures
the effect ofN
on adoption
propensities, holdingn
constant, isimmune
to false positives, but will tend to understate thenetwork
effect
and
may
yield a false negative.An
alternativeway
to get at thenetwork
effect is to holdn/N
=
v constantrather
than
n, that is, to hold constant thenumber
of depositors per locationand
increase the
number
of locations. Dividing (2)by
n
gives:M
„+
KN)] >
md-^+di
+
[cm-^T+i^
n
vHolding
v constantremoves
thedownward
biasfrom
the additional location-specificcost.
However, because
increasingN
while holding v constantadds
both a
locationand
v depositors to the network,an
upward
bias is introduced.The
term
involvingS
isnow
decreasing inn
because
system
costs are spread overmore
depositors.Thus
ifbanks with
more
locations (holding v constant) arefound
tohave
a higher propensitytoadopt
this couldsimplybe
due
to increasingreturns to scale insystem
costs
and
notdue
to thenetwork
effect. This test, then, will overstate thenetwork
effect
and
can
yield false positives but not false negatives.In
summary,
examining
the propensity toadopt
holdingn
constant understates theimpact
of thenetwork
effect, while holdingn/N
constant overstates it.As
described in Section 5,
we
test for the presence ofa network
effectby
holdingn
constant,
then
use thesetwo
assessments tobound
themagnitude
of theimpact
ofthe
network
effect.The
size of thenetwork
effect willbe
closer to theupper
bound
estimate if location-specific costs are
more
important
than
system
costs.We
have
assumed
thus far that thereisno
variationin the valuationofan
ATM
network
among
banks with
thesame
number
of depositorsand
ATM
locations. In practice, however, this is unlikely tobe
the case. Forexample,
some
banks might
Alternatively, the benefits of after-hour
banking might be
greater forsome
banks,such
as those situated in the suburbs,than
for others. In this case,among
thebanks
with a givennumber
of depositorsand
locations, thebanks
forwhom
suchidiosyncratic benefits are the greatest will
adopt
earliest while the others wait.To
take account of such differencesamong
banks, let et- (E(ei)
—
0) representthe deviation of the per period profits of
bank
ifrom
themean
profit ofbanks with
the
same
number
of depositorsand
locations. In this case the net present value ofa
bank's profitfrom adopting
at timeT
is:and
Equation
(2)becomes:
e,
>
C(N,
T)
-
SC(N,
T
+
1)-
\n[a+
b(N)]gT
, (3) i.e.,banks with
idiosyncratically large net benefitsadopt
early while others wait.The
smallestT
;=
T(n,
N,
e;) that satisfies (3) is the optimaladoption
date for theith bank.
In general the rate of adoption
may
change
over time.This
depends on
how
the cost or benefits of adoptionchange
over timeand
on
how
e; is distributed.To
see this, useEquation
(3) to define:e*i(n,
N, T)
=
C{N,
T)
-
6C(N,
T +
1)-
Xn[a+
b(N)]gT
. (4)Then
e*(n,N,T)
is the e; of thebank
withn
depositorand
N
locations that isjustindifferent
between adopting
and
not adoptingat time T.Then
theprobabilitythat abank
with
n
depositorsand
N
locations adopts in periodT
(i.e., thehazard
rateat period
T)
is:H[e*(n,N,T
+
l)]-H[e*(n,N,T)}
l-H[e*(n,N,T)}
' l°Jwhere
H(-) is the cumulative distribution function for e. If, asassumed
above, the benefits ofadopting
relative to costs increase over time, the right-hand-sideof equation (4) decreases with T. Therefore
even
if e is uniformly distributed so that thenumerator
of (5) is constant over time, thedenominator
declines in T.As
a result,
more
banks
find it profitable toadopt
each periodthan
did the periodbefore.
Moreover,
if e, isnormally
distributed, say, then in the early periodswhen
theNormal
density isan
increasing functioneven
more
banks
find it profitable toadopt each
periodthan
the period before so that thistendency
is reinforced. Forboth
of these reasonswe
expect to find positive durationdependence
in thehazard
rate.
3.
Estimation
Models
Equation
(4) implies thatadoption
time, conditionalon
a bank's observable charac-teristics, is arandom
variable.The
choice ofan
estimationmodel
involves choosinga
distribution foradoption
dates. In addition,because
our
observations ofadoption
times are right-censored, the estimationmodel must
accommodate
censoring.The
strategy
we
follow is to estimatestandard
duration models.These
models
easilyincorporate censored observations
and
yield readily interpretablereduced
form
pa-rameters.9
The
durationmodel
which
is themain
focus ofour
analysisassumes
that thetime
untiladoption
forbank
i conditionalon
its characteristics follows aWeibull
distribution. Let Xibe
the vector ofobserved characteristics forbank
iand
/?
be
theunknown
coefficients.Then
theprobability thatbank
iadopts
beforetime
T
is given by:For
convenience,we
make
the standardassumption
that ip^x'^)can
be
written asAn
attractive feature of the Weibull distribution is that thecomputation
ofthe effects of the covariates
on
adoption probabilitiesfrom parameter
estimates isrelatively simple.
The
hazard
rate is (l/f)ip(x'i(3)t
1~1/~t
.
Under
theassumption
that ^(x'jP)
—
ex <P, the estimated coefficients are simply the effect ofx
on
the logof the
hazard
rate.The
Weibull distribution allows thehazard
rate for a givenbank
tochange monotonically
over time. This probability increases, declines, or is9
For a discussion of duration
models
in general, see Kiefer (1988),and
foran
overview
of applying these techniques to technology diffusion, seeRose
and Joskow
(1990).
constant as
7
is less than, greater than, or equal to one.10For
reasons discussed inSection 2,
we
expect to find7
<
1.The
Weibull, however, constrains thehazard
rate intwo
potentiallyimportant
ways. First, it requires that durationdependence be monotonic.
A
standard
em-pirical regularity in diffusionstudies is
an
initially increasing then declininghazard
rate. Since
we
have data on
only the early years of the diffusion process forATMs,
it
seems
likely that a functionalform
that allows a monotonically increasing ratewill
be
adequate. Nonetheless, amore
general functionalform
is a useful checkon
the
Weibull
results. Second, the Weibull (incommon
with
the othermembers
ofthe family of proportional
hazard models)
constrains the relativehazard
rates ofany
two
banks
tobe
constant over time. Forexample,
the ratio of thehazard
rateof a
bank
with
many
depositorsand
many
locations to thehazard
rate of abank
with
many
depositorsand
one
location isassumed
tobe
time invariant.Suppose,
however, that the date ofadoption conditionalon
bank
characteristics isNormally
distributed.
Then
this ratiomight be
relatively large earlyon
and
decline overtime.
This
couldhappen
because, with aNormal
distribution, the densityfunc-tion of the
many-location
bank
can
be
declining while the density function for thesingle-location
bank
is increasing.To
test the results for sensitivity to the constraintsimposed
by
the Weibull,we
estimate a durationmodel
inwhich
the underlyingadoption
date distributionis
assumed
tobe
log-logistic.The
log-logistic distribution allows anon-monotonic
hazard
rateand
allows relativehazard
rates tochange
over time. Itapproximates
a
model
inwhich
the log of adoption dates isNormally
distributed. For the log-logistic, the probability thatbank
i hasan
adoption date earlierthan
T
is given by:1_
Ii
+
ti/7^(x;/?)J'10
The
Weibull
is
a
generalization of the exponential distributionused
in theHannan
and McDowell
(1984, 1987) analysis. It collapses to the exponentialwhen
7
=
1.Although
theyassume
a time invariant underlyinghazard
rate,Hannan
and
McDowell
usetime
varying covariates so that thehazard
ratecan
change
asbank
characteristicschange
over time.We
have
chosenan
alternativeapproach
ofallowing the
hazard
rate tobe
a function of t directlyand
using each bank's 1971characteristics.
With
this approach,bank
characteristics are necessarily exogenous.where
we
assume
again that i/>(x't(3)
=
exp(x[/3).The
hazard
rate isl
+
^lx'ipph
For
7
lessthan
1, this functionalform
hasan
underlyinghazard
function thatinitially increases
and
then decreases over time. If7
is greaterthan
orequal to one,the underlying
hazard
function has negative durationdependence.
For
both
distributions, the likelihood function for observationson
m
banks
is:m
Y[f(x'
ip,T,
7
)d
<[l-F(x'
ip,T
n
)] 1-
diwhere
d
isan
indicator variable equal toone
ifthe firm adoptsand
/(•) (F(-)) is the density function (cumulative distribution function) for theWeibull
or log-logisticdistribution.
The
firstterm
is the contribution to the likelihood of a firmobserved
to
adopt
attime
T; thesecond
term
is the contribution of a firm failing toadopt
prior to
time
T
afterwhich
it isno
longer observed.Both
thesemodels
assume
a distribution foradoption
times conditionalon
bank
characteristics. If these parameterizations fit thedata
badly, the coefficientestimates
may
be
adversely affected.We
thereforecompare
theseparametric
es-timates to results
from
anonparametric (Cox)
partial-likelihood estimator.This
estimatormakes
no assumption about
the underlyingdistribution ofadoption
times,but
insteaduses the proportionalhazard
model
assumption
that the ratiosofhazard
rates for
any two banks
aretime
invariantand
estimates the relative probabilities.4.
Data
Testing the hypothesis that
network
sizematters
given thenumber
of depositorsrequires variables that capture
network
size,number
of depositors,and
date ofadoption.
This
section describes these variables as well as variablesused
to controlfor other
bank
characteristics thatmight
affectadoption
probabilitiesand
be
cor-relatedwith
the variables ofinterest. Descriptive statistics for the variablesused
inthe analysis
appear
inTable
1.The
data
base includes informationon
adoption
dates,bank
characteristicsand
state regulations.
Because adoption
is presumptivelymore
likely inurban
areas,the
sample
was
restricted tocommercial banks
operating in acounty
thatwas
part ofan
SMSA
orhad
a population center of at least 25,000 in 1972.This
subset of allcommercial banks
in operationbetween
1971and
1979was
further restricted toconform
to the availableadoption
dataand
to capturevariationinnetwork
size.The
finalsample
includes allcommercial
banks
that satisfied the geographic criterion in1971
and
that existedthroughout
the 1971-1979sample
period.The
adoption data
come
from
surveys of allcommercial
banks conducted by
the Federal Deposit Insurance
Corporation
in 1976and
1979.The
1976
survey asks the year thebank
first installed at leastone
ATM.
The
1979 survey askswhether
thebank
has installedan
ATM
by
the 1979sample
date.Combining
these surveysgives a date offirst
adoption
forbanks
adopting prior to1977
and
identifiesbanks
adopting between 1976
and
1979.Year
of adoption for these later adopterswas
collected
by
asupplementary
surveyconducted by
Hannan
and
McDowell
(1987).n
The
date ofadoption
is the year thebank
first installed at leastone
ATM.
Because
the surveys cover onlybanks
existing at the survey dates, consistency requires thatour
sample be
restricted tobanks
existing in 1976and
1979. Sincewe
use 1971characteristics data, the
sample
also is restricted tobanks
in existenceby
1971.The
adoption data were
merged
withdata
on
firm characteristicsmaintained
by
the Federal ReserveBoard
in theReport
ofConditionand Income and
theSum-mary
of Deposits.These
sourceshave
detailed balance sheetand
othersummary
information
on
allcommercial
banks
operating in theUnited
States. In particular,they contain the best available information
on
number
of depositorsand
network
size as well as information
used
to control forother dimensions ofbank
heterogene-ity.
In the 1990s
ATMs
arecommonly
linked in regionaland
national networks. For at leastsome
ATM
transactions then, the relevantnetwork
size isnow
the sizeof the interbank network. In the 1970s, however, interbank connections
were
un-11
The
raw
surveydata
and
thesupplementary
informationon
lateradopterswere
generously given tousby
Hannan
and
McDowell.
Our
sample
hasbeen
constructedto
be
roughly consistentwith
theirs. Despite their efforts,adoption
dates are notavailable for
87 banks
known
tohave
adopted
and
otherwise consistentwith
thesample
definition.Except
where
otherwise noted, thesebanks have
been
dropped
from
the sample.common.
Many
of the earlymachines were independent
units; theywere
not fullyconnected with
the bank'sdata
system, let alonean
interbank system. Further,in the early seventies
ATM
producershad
not yet achieved a technologicalstan-dard
thatwould
make
machines
compatible. Legal issueswith
respect to sharedATMs
alsoslowed
thedevelopment
of interbank networks. Interstatebanking
was
not
permitted
in this periodand
many
state's regulated thenumber
and
location ofbank
branches.Allowing
interbanknetworks
would
clearly affect the existingregulatory regimes,
and
sharingwas
delayed while regulators decidedhow
itshould
be
managed.
Stateand
federal rulingson
interbanknetworks
have
reflectedboth
a concern
that large, singlebank
systems might
reinforce themarket
dominance
of
banks
already largeand
a countervailing concern that cooperativearrangements
among
banks might
create collusive pricing.12The
combination
ofpotential orac-tual legal constraints
and
therudimentary
state of thenew
technologymeant
that interbanknetworks were
notimportant
in the 1970s.As
a result, thenetwork
sizerelevant to a cardholder
was
the size ofher bank's proprietary network.13For these single
bank
networks, the relevantnetwork
size is thenumber
ofATM
locations the firmexpected
tohave
in equilibriumwhen
making
theadoption
deci-sion.This
number,
however, is inherently unobservable.Even
if thedata
reportedthe
number
ofATM
locations for eachbank
in each year, thesenumbers would
notnecessarily include the
planned
equilibriumnumber.
14We
therefore use thenumber
ofbranches
abank
has(BRANCH)
as aproxy
forexpected network
size.BRANCH
12
For a review of the law
on
interbank networks, see Felgran (1984). 13If
banks
anticipated thatATM
networks
would
ultimatelybe
interlinked, thiswould
ofcourseaffect theirestimatesofthe net present value of benefits inEquation
(1).
However, provided
that in the 1970sbanks
believed thatsuch
interlinkingwould
notoccur
until the 1980s, such benefitswould
be
irrelevant to thetiming
of
adoption
decision representedby Equation
(2).However
the analysis in Section2 ignores possible competitive
advantages
thatmight
accrue tobanks
thatadopt
early.
For
example,
iffirms that pioneerinterbanknetworks
are able to extractsome
of the rentsfrom
the creation of such networks,and
ifbanks with
many
branches
who
adopt
early are well-positionedin the competition toform
interbank networks, thosebanks
would
have
an
added
incentive toadopt
early.We
hope
to considersuch
competitive incentives to adopt,which
are largely ignored in this paper, infuture work.
14
In fact, the
data
do
not report thenumber
ofATM
locations.Nor
is thenumber
ofATMs
installed systematically available.is
an
excellentproxy
ifbanks
typically place at leastone
ATM
ineach
branch
and
place relatively
few
orno
ATMs
elsewhere.Banks
tend to placeATMs
in branches for several reasons. Installingand
maintaining
ATMs
on
the premises of existing branchesmay
be
less expensivethan
at off-premise locations.
Consumers
alsomay
-at least in the earlydays
ofATM
use covered in this study -have
feltmore
comfortable usingmachines
locatedwhere
they could get assistance with usage problems. Further, the legal status of
off-premise
placement
was
unresolved for a substantial portion of thesample
period.State regulatory agencies
and
legislatures controlwhether
off-premiseplacement
is allowed for state chartered banks. For national banks, off-premise
placement
is controlledby
theComptroller
ofthe Currency. In 1979, theComptroller
ruled thatoff-premise
placement by
nationalbanks
would be
allowed.15Some
state authoritiesacted to allow off-premise
placement
prior to the Federal rulingand
some
tied state regulations to the Federal standard. Still othershad
not yet issued regulations foroff-premise
placement
by
1979.16 Until off-premiseplacement
was
authorized, thenumber
ofbranches
was
aclearupper
bound
on network
size.Even
when
off-premiseplacement
was
allowed, on-premiseplacement
was
more
common.
Commentary
inthe trade press during this period suggests that
banks
eventually placeATMs
inmost
branches
so that thenumber
of branches is also agood
lowerbound.
Because
states regulate branching, the distribution of branches perbank
willvary across states. In
some
states, branching is not allowed;banks can have
no
more
than
a singlebanking
office.Because
there isno
variation innetwork
size inthese states,
banks
in these states are not included in the sample.17As
a result,the
2293
banks
in thesample
are distributed over the 37 states inwhich
multiplebranches
were
allowed in 1971.Among
these states, 19 placedno
restrictionson
15
This
rulingmeant
that the Federalgovernment no
longerhad
an
interest inregulating
ATMs.
As
a result, nationaldata
on
ATMs
were
not collected after 1979.16
Most
states regulate off-premiseplacement
insome
fashioneven
where
it is allowed. Forexample, banks
may
be
required to get approval foreach
off-premise location or to share off-premise locationswith
rival banks.17
In principle, these single
branch
banks can be
included in the analysis topro-vide additional information
on
the effect of variation in thenumber
of depositorson
adoption
probabilities.But
includingthem
does not substantively affect theparameter
estimates.the
number
or location ofbranches.We
refer to these states as "unrestricted".The
remaining
18 stateshad
some
limitationon
thenumber
or location of branches.Banks
in these "limited" statesmay
be
required to restrictbranching
to, say,a
single
county
or to refrainfrom
placing abranch
in a smallcommunity
alreadyserved
by
a competitor.18Ideally, the
n
inEquation
(1)would
be
implemented
as thenumber
ofdeposi-tors for
whom
ATM
transactionshave
value.A
closeproxy
might
be
thenumber
ofdepositors
with
personal checking accounts.However,
there areno data
availableon
thenumber
of accounts ofany
type.19The
next bestproxy
is total depositsby
customers
who
would
usean
ATM.
Thisproxy
might
be
affectedby
variation in thesize of accounts across banks.
The
closest availableproxy
is"demand
depositsby
individuals, partnerships,
and
corporations"(DEPOSITS).
DEPOSITS
specificallyexcludes
time
and
savings deposits (certificates of depositsand
savings accounts,for
example)
and
other less liquid holdings, as well as deposits held for otherbanks
or the public sector, but includes
commercial
demand
accountseven
though
theseaccounts
probably
do
not generateATM
demand.
The
extent towhich
DEPOSITS
is a
good
proxy
forn
depends
on
how much
variation there is in the proportion ofindividual accounts in
DEPOSITS
across banks.Four
additional variables areused
tocontrol for other factors thatmight
affectadoption:
wage
in the area(WAGE),
laborexpense
peremployee
(WB/L),
the averagenumber
ofbranches
perbank
in the state(PROPBR),
and
product
mix
(PRODMDC).
The
wage
variable is included to control for variations inATM
valuearising
from
variations in labor cost. Iftellers aremore
expensive, technology thatcan
substitute for tellers shouldbe
more
attractive. In this case, higherwages
should
promote
ATM
adoption.On
the other hand, the wage, asa
measure
ofaverage
income
in the bank's area,may
alsobe
correlatedwith
the average size 18The
data used
to classify states with respect to
branching
regulationswere
provided
by
theConference
of StateBank
Supervisors.Two
stateschanged from
limited to unrestricted regulation during the
sample
period.Because
substantivechanges
inbranching
regulationsmight change adoption
behavior, observations forbanks
in these states are treated as censored at the date of change.19
The
only
data
on
number
ofaccountscome
from
the FunctionalCost
Analysisreports.
These
data
are not publicly available in disaggregateform
and
cover onlya
very small,nonrandom
sample
of banks.of checking accounts. If people with higher
income
typically hold largerdemand
deposits, theWAGE
variablemay
pickup some
variationinthe relationshipbetween
DEPOSITS
and
thenumber
ofcustomers forwhom ATMs
are of value.The
wage
used
is the averagemanufacturing
wage
for 1977.20The
bank's laborexpense
peremployee
is total expenditureson
salariesand
benefits divided
by
thenumber
of employees.There
issome
evidence that thisvariable is high in concentrated markets,
presumably because
of rent sharingwith
employees
(Rhoades
1980). In that case,banks
with high values ofWB/L
may
be
more
likely toadopt because
theycan
extract a larger share of the resultingconsumer
value (i.e., theyhave
higher As inEquation
(1)than
banks
in less con-centrated markets).On
the other hand,WB/L
might
capture variation in themix
ofbanks' employees. It is possible, forexample, that a
bank
with
a relatively high value forWB/L
has fewer relativelylow-wage
tellersand
more
relativelyhigh-wage
commercial
accountmanagers
or investment advisors.A
high valueofWB/L
might
therefore indicate a low proportion of individual depositors and, therefore, a
low
propensity to adopt.
The
variablePROPBR
is included to absorb variation in statebranching
reg-ulations.
Within
the limit category there is substantial variation in the severity ofthe
branching
restrictions.As
a result, the averagenumber
ofbranches
perbank
in limit states varies
from
lessthan
2 tomore
than
8.21Increasinglyrestrictivebranching regulationssuggest that thestand-alone value
of
adoption
(a inEquation
(1))might
be
higher.The
reason for this is that adepositor at a
bank
with, say, a singlebranch
hasno
substitute for visiting that bank's single location duringnormal
business hours.By
contrast, a depositor ata
multi-branchbank
may
at leastbe
able to substitute a transaction duringnormal
20
As
reported in the Cityand County
Data
Book.
21
Wisconsin
banks
average lessthan
1.5. branches per bank,and
branching
isallowed only within the
same
county
as the bank'smain
officeand
then
only ifthere is
no
otherbank
operating in that municipality or within three miles of theproposed
branch.New
York, in contrast, hasmore
than
eightbranches
perbank
and
allows statewidebranching
except thata
bank
cannot
branch
in atown
with
apopulation
of50,000 or less inwhich
anotherbank
has itsmain
office.The number
of
branches
perbank
is a statewide averagebased
on
all thebanks
in the state, notjust those in
our
sample.hours
atanother
branch
for a transaction at her usual branch. Or,more
generally,banks
whose
depositorswould
feel constrained if they could onlybank
at theirusual
branch
duringdaytime
hoursmight
findit in theirinterests toopen
additional branches. Sincerestrictedbanks
are unabletoopen
asmany
branches
astheywould
like, they
might
more
readily turn toATMs
as away
to relievea
tightlybinding
constraint.
As
a result, since a lower value ofPROPBR
indicates amore
restrictiveregulatory
environment,
PROPBR
shouldhave
a negative effecton
adoption.There
is,
however,
a potentially offsetting competitive effect. If abank
operates ina
state in
which
there aremany
multi-branch competitors,competition
may
push
abank
toadopt
earlierthan
itwould
if it faced a less competitiveenvironment.
Inthat case,
PROPBR
might be
positively correlatedwith
adoption. In unrestrictedstates the regulatory effect should
be
absent so thatPROPBR
should reflect thecompetitive effect.
We
therefore expect a positive coefficient there. In the limitedstates,
however,
both
effectsmight be
present. If the regulatory effectoutweighs
the competitive effect in those states, the coefficient willbe
negative.Finally, following
Hannan
and
McDowell
(1984)we
include aproduct
mix
vari-able,PRODMIX,
which
we
measure
as the ratio ofDEPOSITS
to thesum
of all deposits.The
denominator,
therefore, includes all timeand
savings depositsand
deposits held for the public sector as wellas the
commercial
and
individualdemand
depositsappearing
in the numerator.22 Since in the 1970sATMs
were used mainly
for transactions involving checking accounts,
banks
whose
total deposits includea larger share of individual
and
commercial
demand
depositsmight have
a higherdemand
forATM
services. In that casePRODMIX
would
have
apositive coefficient.Table
1 presentssummary
statistics for the entiresample
ofbanks
inmulti-branching
statesand
for the limitedand
unrestricted subsamples.The
averagebank
has
over $36 million inDEPOSITS.
As
might
be
expected,banks
in statesthat
do
not restrictbranching
are largeron
averagethan
thosein stateswith
limited branching.As
a
result, there aremany
more
banks
in the 18 limited statesthan
inthe 19 unrestricted states.
The
size distribution ofbanks
isskewed
to the right: the22
Alternative
product
mix
ratioswere used
inunreported
regressions, including the ratio ofDEPOSITS
to the bank's total assets.The
resultswere
substantivelyunaffected.
largest
banks have
DEPOSITS
over $5,000 million, but only 22banks have
deposits over$500
million,and
75 percent of thebanks have
DEPOSITS
under
$16 million.While
the averagebank
acrossboth
regulatory regimes has slightlymore
than
sixbranches, the averageunrestricted
bank
has three times asmany
branches
as the average limited bank.This
variation is also reflected in thePROPBR
variable thatreports the average
number
ofbranches forallbanks
inthe state.The
PROPBR
val-ues are
somewhat
lowerthan
thesample
averages forBRANCH
because
PROPBR
includes
banks
operating only in less denselypopulated
areasexcluded
from
thesample. Like
DEPOSITS,
BRANCH
isskewed
to the right: thebank
with
themost
branches
(WellsFargo
in California) has 1013 branches, but the next highestnumber
is 443,and
75 percent ofthebanks have
fewerthan
five branches.Because
the
DEPOSITS
and
BRANCH
variableshave
similarlyskewed
distributions, thereis
much
less variation in the average forDEPOSITS
perBRANCH
across regimes.The
limitedbranching
stateshave banks
that average $5 million perbranch
versus$3.6 million in unrestricted branching states.
The
adoption
rate during thesample
period is 17-19 percentand
is higher inunrestricted states.
Among
adopting banks, the average time untiladoption
is 5.5years
with
unrestrictedbanks
adopting earlierthan
limitedbanks
(4.7 versus 5.7).5.
Results
In this section
we
present the empirical evidence for anetwork
effecton
adoption
rates.
To
develop theargument,
we
focus initiallyon
the relationshipbetween
thenumber
ofdepositors, as proxiedby
DEPOSITS,
and
the propensity toadopt
early.Next, the
main
results are presentedby
introducing thenumber
ofbranches
as aproxy
forexpected network
size.These
results are first presented as estimatesfrom
a
Weibull
specification.To
test forrobustness tofunctionalform, theWeibull
resultsare
then
compared
toestimatesbased
on
theCox
partial-likelihoodand
log-logisticforms. Finally, the possibility that the observed relationship
between
number
ofbranches
and
propensity toadopt
is simplyan
order statistic effect is addressed.Weibull
estimates of the relationshipbetween
adoptionand
number
ofdepos-itors are reported in
Table
2.Pooled
estimates forbanks
in all states permitting multiplebranches
and
separate estimatesforbanks
inlimitedand
unrestricted statesare reported.
The
results are consistentwith
the findings ofHannan
and
McDowell:
the coefficientsimply
that the log of thehazard
rate isan
increasing,concave
func-tion of
DEPOSITS.
The
estimates are precise,and
the pattern is consistent acrossregulatory regimes.
As
reported at thebottom
of the table, these estimatesimply
that increasing
DEPOSITS
by
$1 millionabove
thesample
mean
leads toabout
an
0.5 percent increase in thehazard
rate in the pooled regression.The
increase ismore
marked
in limitedthan
unrestricted states,perhaps because
banks
in limitedstates
have
much
smallerDEPOSITS
on
averageand
the log of thehazard
rate isconcave
inDEPOSITS.
23When
BRANCH
is included in the regressions it is entered as a quadraticto allow it to
have
a curvatureindependent
ofDEPOSITS.
As
suggestedby
themodel
in Section 2,we
also includeDEPOSITS/BRANCH
to account forlocation-specific costs of installing
ATMs.
The
signon
DEPOSITS/BRANCH
should
be
positive,
and
if location-specific costs are high relative to thesystem
fixed costs, this coefficientmight
capture a large share of the effect ofDEPOSITS.
For
thepooled
regression, the coefficientson
theBRANCH
terms
imply
thatadding a
branch
has - at best -no
effecton
the adoption rate.The
derivative ofthelog ofthe
hazard
ratewith
respect tobranch
is negativewith
a largestandard
error.The
estimates forbanks
in unrestricted states, however, tell a very different story.The
branch
derivative is positive in this regime. But, including theBRANCH
variables
changes
the sign of theDEPOSITS
derivative: theapparent
effect ofan
increase inDEPOSITS
holdingnumber
of branches constant is toreduce
theadoption
rate.This
counterintuitive resultand
thepoor showing
ofBRANCH
inthe
pooled
regressionappear
tobe
the results ofnear colinearityofDEPOSITS
and
BRANCH
in the unrestricted states.The
correlation coefficientbetween
BRANCH
and
DEPOSITS
forbanks
inunrestricted states is .98. Apparently,
when
branching
is unrestricted,banks
add
depositors
by adding
branches.The
effect ofnear colinearity is reflectedin thelargeincrease in the
standard
errorson
theDEPOSITS
coefficientswhen
BRANCH
isadded. In (unreported) regressions includingonly linear
DEPOSITS
and
BRANCH
23
All reported derivatives areevaluated at the