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New Product Introductions, Trademarked Advertising and Market Value:
An Econometric Analysis of Coca-Cola vs Pepsi Competition
Andrea Fosfuri♣
and Marco S. Giarratana♦♦♦♦
First draft: March 2005; this version: November 2006
Abstract
This article analyzes how the financial-market value of a firm is influenced by the actions of its rivals.
We investigate the competition in the carbonated soft drink market between 1999 and 2003, a period
characterized by price stability and an almost duopoly of Coca-Cola and Pespi. We focus on new
product announcements as a proxy of new product introductions and on filed trademarks as a measure
of advertising efforts. Our empirical study yields three important results. First, we find that rival
efforts in product introduction produce a negative impact on a classical measure of firm financial-
market value, the Tobin's q. More interestingly, our evidence highlights that the effect of rival
advertising efforts on a firm’s financial-market value is positive. Finally, we find that the channels
through which these two strategic tools affect a firm’s Tobin’s q are different. Trademarked
advertising influences mainly total market demand, while new product introductions affect directly the
distribution of market shares.
Keywords: Production Introduction, Advertising, Firm Value, Rivalry
♣ Department of Business Administration, Universidad Carlos III de Madrid, [email protected]
♦ Department of Business Administration, Universidad Carlos III de Madrid, [email protected]
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1. Introduction
Both the financial and the management literature show that a firm’s actions and investments influence
its market value (Wernerfelt and Montgomery 1988; Bayus et al. 2003; Hall et al. 2005). This body of
research highlights extensively a wide spectrum of competitive moves that range from price changes
to new product releases, from alliance formation to patented technological innovations.
Firms’ actions are the result of a strategic decision process that often time is ignited by the
information available outside firm boundaries (Mintzberg 1978). Therefore, firms not only are
constantly engaged in detecting new competitive actions, but also in responding to rival moves with
strategic reactions. How firms react to competitive stimuli depends indeed on the nature of the
stimulus itself. Porter (1980) argues that when firm moves threaten the profitability of other
competitors, countermoves must be expected. By contrast, cooperative or non-threatening actions
trigger different competitive responses.
However, the empirical evidence that analyzes how a firm’s market value responds to rival
moves is rather underdeveloped. A recent paper by Silverman and McGahan (2006) focuses on the
effect of patents granted to competitors. Other scholars have looked at alliances (Das, Sen and
Sengupta 1998) and price changes (Chen and MacMillan 1992). To the best of our knowledge, no
research has been conducted on the effect on a firm’s market value of rival moves along non-price
dimensions of the marketing mix. We tackle this issue by seeking to understand how rival moves in
new product introductions and advertising affect a firm’s market value. This is an important research
question because the expected effect is not clear-cut. Brandenburger and Nabeluff (1997) argue that
strategic postures of rival firms go behind the mere market-stealing actions. For example, competitors
might be key to sustain market demand, making a product more attractive to customers, thereby
benefiting all the players in an industry. Thus, while some rival actions may increase a firm’s market
value, others may dampen it. That granted, the perception of different levels of aggressiveness in the
rival moves appear an almost necessary requirement for strategy makers.
3
Empirically, we investigate our surmises by analyzing the Carbonated Soft Drink (CSD)
industry from January 1999 to December 2003, an USD60 billions industry in the US alone. The
choice of the market makes a natural experiment possible: During the sample period, the CSD market
is virtually a duopoly (Coca-Cola and Pepsi controlled more than 75% of total sales) characterized by
relatively high price stability (Dubè 2004). The duopoly condition allows us to investigate with greater
precision the effects of strategic actions and reactions on the two competitors' market value. Moreover,
since in the CSD market prices are not major tools of competition, we are able to isolate more
effectively the impact of new product introductions and advertising efforts. It is worthwhile noting that
Coca-Cola and Pepsi invest together more than USD3 billions in advertising each year.
Our empirical results show that the impact of such rival actions on a firm’s financial-market
value is dichotomous. We find that a rival effort in product innovation has a clear negative impact on a
firm's financial-market value, while promotion efforts have a positive effect. A second rather
interesting empirical finding also emerges: The two strategic tools impact on a firm’s financial-market
value through different channels. While rival promotion efforts affect the firm’s financial-market
value through total demand, rival new product introductions act directly on the firm’s market share.
The article provides the following contributions to the literature. First, we enrich the evidence
on the impacts of marketing investments of a firm’s financial-market value, that is somewhat less
extensive compared to that focused on other competitive moves, for instance, R&D efforts. For
notable exceptions see Pauwels et al. (2004) and Srinivasan et al. (2006). Moreover, this constitutes
one of the few studies, which highlights the impact of rival strategic moves on a firm’s financial-
market value, especially within the marketing literature. In this respect, product releases and
advertising can theoretically take the form of defensive or offensive strategic tools (Bayus and Putsis
1999; Kadiyali et al. 1999; Shaffer and Zhang 2002). Our evidence suggests that in the case of Coca-
Cola and Pepsi the non-threatening effect prevails for advertising, the aggressive for new product
introductions. Although this finding might be specific to the CSD market, the fact that advertising
efforts are generally less aggressive than product innovation could be a more general insight.
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Additionally, it is worth noting that, although competition between Coca-Cola and Pepsi has
been analyzed elsewhere (Chintagunta and Vilcassim 1992; Golan et al. 2000), we offer two
improvements with respect to the extant literature. First, we utilize both product and advertising efforts
of the firm and its direct rival. Second, we can count on higher frequency data during a period of non-
price competition in a specific niche where the two major firms constitute almost a duopoly. This
increased empirical flexibility is due to the use of trademarks filed at the US Patent and Trademark
Office (USPTO) as a proxy for advertising efforts. This is a novel measure that has been only recently
employed in empirical studies (Seethamraju 2003; Fosfuri and Giarratana 2007). Trademarks are
available at high frequency with a precise product niche classification. Higher frequency data allow a
better match with the promotion process, which is characterized by pulsing, i.e. firms systematically
switch promotion on and off at a high frequency (Ofek and Sarvary 2003).
Interesting enough, the article shades also new light on the channels through which new
product introductions and advertising efforts influence a firm’s market value. We show that the two
strategic actions act through separated channels, advertising mostly affects total demand, while
product innovation acts directly on the distribution of market shares.
The remainder of the paper is organized as follows. The next section lays down the theoretical
model and defines our hypotheses. Section 3 offers a brief description of the CSD market. Section 4
presents the data, and our empirical methodology. Section 5 shows the results and discusses several
robustness checks. Section 6 concludes.
2. Theory and hypotheses
Marketing actions can occur along different dimensions of the marketing mix: price, product,
promotion and position (Levitt 1980). Such actions might affect the firm’s and its rivals’ market
values in different ways. Due to the ease in data collection, pricing strategies have been largely
analysed in the literature (i.e. Merrilees 1983) even if they do not constitute the prime variable of
competition in many markets in which demand is more brand-sensible and/or in which firms try to
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avoid price wars (Ilinitch et al. 1996). The easy-to-eat breakfast cereal market (Corts 1996) and the
beauty and health products are classical examples (Koehn 2001).
The analysis of the other dimensions of the marketing mix is rising only recently, especially
for new product releases and advertising efforts (see, for instance, Azoulay 2002; Bayus et al. 2003;
Hui 2004).1 New product introductions modify the space of observable characteristics, such as size,
shape, colour, weight, design material, reliability, and taste that are relevant to customers' preferences
and condition their choice processes. Advertising is linked to the image and positioning perceived by
the consumers beyond the physical features (Miniard et al. 1993). Advertising is build upon a complex
constellation of psychological attributes that the consumer assigns from purchasing, owing, and
consuming a particular product. It involves social, emotional, psychological, and esthetical
considerations. To a great extent, advertising creates brand power that influences and reinforces
customer perceptual connections among products, identity and lifestyle (Upshaw 1995).
The effects on a firm’s market value of its own product and advertising efforts are quite
straightforward. Several works propose sound empirical evidence on the positive returns of these two
manoeuvres (Bayus et al. 2003; Pawels et al. 2004; Srinivasan et al. 2006). However, the way firms
structure their product and advertising strategies depends largely on the information that comes from
their environment, being rival actions a salient part of this information (Minztberg 1978; Porter 1980).
Coherent empirical evidence on this latter point is missing. Rival actions could produce diverse
impacts on a firm’s market value because they could considerably exhibit distinct levels of
aggressiveness and cooperation (Brandenburger and Nabeluff 1997). Therefore, our theoretical
argument will leave in the background the effects of a firm’s product and advertising efforts on its
market value, while it will focus on the effect of rivals’ actions.
To structure the discussion, let Vit be the market value of firm i at time t, that is the net present
value of its future stream of profits. Other things equal, Vit depends positively on firm i’s market share
and on total demand. Precisely, market value increases if the firm attains a larger market share and/or
if total demand for the product expands. This could be easily modelled (more details in the Appendix)
1 Position is normally seen as a combination of the other three variables.
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by assuming, for instance, that the number of goods sold by firm i follows a Poisson process where the
Poisson’s λ and T parameter (the rate of number of occurrences per unit of time and the time duration)
are interpreted as firm i‘s market share and total demand, respectively (see also Russell and Kamakura
1994). We keep this in mind, since in the following arguments, the effects on a firm’s market value of
rival product introductions and advertising will be channelled through these two different avenues.
New Product Introduction. We analyze the impact of rival efforts to expand, modify and deepen their
product offering on firm i’s market value. First consider firm i’s market share. A larger number of
varieties by a rival produces a reduction in competitors’ market shares in almost any model of product
differentiation (Champsaur and Rochet 1989; Kekre and Srinivasan 1990; Baye et al. 1996).
Consumers might switch to the new varieties offered by the rival because they satisfy better their
tastes or because of their increased quality. In fact, firms, through continuous refinements of their
products, can develop versions that adapt and match more closely the needs of their customers. This is
especially important in environments where product introduction usually has a strong customer-driven
component (Schmalensee 2000). As long as some customers are substituting firm i's products for rival
new offerings, then the impact on market share is negative.
Concerning the effect on total demand, by adding new product varieties a firm can attract
customers who try the product for the first time. This is equivalent to build additional location sites in
areas of the Hotelling line where there are un-served consumers (Schmanlensee and Thisse 1987). In
other words, the arrival of products with novel characteristics could induce individuals that have never
bought a product to initiate a process of purchase. However, new costumers usually reveal scarce
brand loyalty and could later spread across different brands, the so-called churn demand (Neslin et al.
2006). This implies that a firm’s product introduction could increase industry demand without
affecting the distribution of market shares or affecting market shares without cannibalizing rival
profits. For example, Bayus and Putsis (1999) find that broad product lines in the personal computer
industry increase the overall demand. In a duopoly market, Kadiyali et al. (1999) highlight that a
firm’s new product introduction increases the revenues of the competitor as well. Indeed, if there is
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enough complementarity among competing branded products it is possible that new product
introductions by rivals might actually increase both a firm’s profits and value.
In sum, product introductions by a rival are likely to decrease a firm’s market share thus
reducing its market value. However, this negative effect might be counterbalanced by a positive effect
due to an increment in total demand. Granted these arguments, our first hypothesis reads:
Hypothesis 1: The net effect of rival product introductions of firm i’s market value is ambiguous.
However, if rival product introductions do not increase total demand, then the expected effect must be
negative.
Advertising efforts. Rivals’ advertising efforts might as well be channelled through an effect on firm
i’s market share and an effect on total demand. The literature classifies advertising in two categories:
generic and brand advertising (Bass et al. 2005). Generic advertising aims to increase primary demand
sales. Brand advertising affects market shares. Therefore, we can identify several potential effects.
Rival generic advertising has a positive effect on a firm’ market value because it increases
total demand. Generic advertising boosts primary demand by attracting new consumers (Berndt et al.
1997), increasing per capita consumption of the product and lengthening the product life cycle
(Friedman and Friedman 1976; Krishnamurthy 2000). Lancaster (1984) claims that it is the most
common effect of advertising.
Rival brand advertising influences directly firm i’s market share. First, brand advertising could
increase the probability that a costumer changes its purchase decision. It provides consumers with
information about the brand’s value proposition that differentiates it from its competitors, thereby
encouraging consumers of other brands to move to the advertised product (Krishnamurthy 2001).
Second, it can induce actual consumers of rival brands to increase the frequency of consumption
(Chaudhuri and Holbrook 2001). Indeed, brand advertising fosters brand loyalty and the consumption
intensity of a particular brand. Therefore, if rival brand advertising increases the consumption among
its costumers, the market shares and the revenues of the rivals will increase accordingly. If this
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happens, the most expected sign on a firm’s market value is negative. This analysis leads to the
following hypothesis:
Hypothesis 2: The net effect of rival advertising efforts of firm i’s market value is ambiguous.
However, if rival advertising efforts do not increase total demand, then the expected effect must be
negative.
3. Market Background
A carbonated soft drink consists of a flavor taste, a sweetener and carbonated water. The production
and distribution of CSDs involve four major participants: 1) suppliers of inputs, 2) concentrate
producers, 3) bottlers, and 4) retail channels. A concentrate producer blends a few raw materials that
for most regular colas consist of caramel coloring, phosphoric and/or citric acid, natural flavors, and
caffeine. Such inputs are produced at competitive prices. Bottlers purchase concentrate, add
carbonated water and high fructose corn syrup, bottle or can the CSD, and deliver it to customer
accounts.
The majority of US CSDs are packaged in metal cans (around 60%), then plastic bottles (about
38%) and glass bottles (2%). Metal cans and bottles are commodities with several manufacturers
competing for a single contract. Almost 60% of the distribution of CSDs in the US takes place either
through food stores or through fountain outlets. CSDs are among the five largest selling product lines
sold by supermarkets, accounting for 3%-4% of food store revenues. Although the industry involves
many different players at different stages of the value chain, two firms stand on top of all others:
Coca-Cola and Pepsi. At this respect, it is interesting to notice that both firms raised concentrate prices
throughout the 1980s and early 1990s, even if the real (inflation-adjusted) retail prices for CSD went
down.
The CSD industry grew in the US at approximately 3% per year over the period 1970-2000. It
is now a USD 60 billion industry (only considering the United States), with the cola segment
9
accounting for about 60%-70% of the market value. Among concentrate producers, Coca-Cola and
Pepsi, controlled 76% of the US CSD market in sales volume in 2000. Coca-Cola was formulated in
1886, and Pepsi-Cola in 1893. Coca-Cola was the uncontested leader in the early history of the CSD
market, with 50% of market share in 1950. During the 1960s Coca-Cola and Pepsi began to
experiment with new cola and non-cola flavors and a variety of packaging options, abandoning their
traditional single product strategy.
Although Coca-Cola and Pepsi have aggressively competed for market shares, they have often
avoided direct price competition. It is illuminating the fact that the announcements of increases in
concentrate price by one company are followed immediately by upwards adjustments by the rival.
According to Roger Enrico, former CEO of Pepsi-Cola, "the warfare must be perceived as a
continuing battle without blood…If the Coca-Cola company didn't exist, we'd pray for someone to
invent them" (Yoffie 2004).
The two firms are instead aggressively competing on non-price dimensions, i.e. product
introduction and advertising. Both product introductions and advertising are important in the CSD
industry. In this industry, new product introduction refers to a change in the physical characteristics of
the product like flavors, ingredients, colors, tastes, packaging, etc. This is a long-played variable in the
Coca-Cola and Pepsi competition: Diet Coke for example was introduced the 8th of July, 1982. The
role of promotion is documented by the heavy investment in advertising and trademarks over time,
usually with innovative and sophisticated marketing campaigns. In the year 2000, Coca-Cola has spent
more than USD 200 million in its flagship brand "Coke Classic" (Yoffie 2004). Snapshot data tell that
Coca-cola filed for the first trademark in 1927 and at the end 2004 has been granted 1,105 trademarks.
Pepsi registered the first trademark in 1907 and at 2004 has filed 1,402 trademarks. As a matter of
fact, from the annual reports, Coca-Cola advertising expenditures top USD 1.9 billion dollars in 2003
and USD 1.8 in 2002. Pepsi shows similar numbers (1.6 and 1.5).
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4. Data and Methodology
4.1. Sample and estimation technique
Data on Coca-Cola and Pepsi were collected on a monthly basis during the period January 1999 -
December 2003. We have therefore 60 observations per firm, and 120 observations in total. Since the
market for soft drinks can be divided in two main niches, namely the Carbonated Soft Drink (Coke,
Pepsi, Sprite, Fanta, Mountain Dew, etc.) and the Non-Carbonated Soft Drink (juices, milky and
energy drinks, tea, coffee, water, etc.), our analysis will be mainly focused on the Carbonated niche
where Coca-Cola and Pepsi detain a stable duopoly position. This allows us to level off the noise of a
too scattered competition.
We chose a monthly base because we think that it matches better the fact that firms tend to
systematically switch promotion on and off at a high frequency (Ofek and Sarvary 2003) and
nonetheless it is still reliable for a robust econometric analysis.2
For clarity of exposition, we build our empirical evidence in three stages. First we estimate the
following regression:
titjtitjtiti AAPPv ,,4,3,2,10, )ln()ln()ln()ln()ln( εγβββββ +∆+++++= (1)
where vi,t is the market value of firm i at time t, subscript i≠j stands for Coca-Cola or Pepsi, P is
product introduction, A is advertising efforts and ∆∆∆∆ is a vector of control variables. This regression
allows us to investigate the direct effect of firm j’s marketing actions (product and advertising) on firm
i‘s market value.
However, the resulting estimations of our core parameters could be the sum of different forces
that claim for a more in-depth exploration.
2 This is not the classical event study that analyses daily market reactions to firms’ announcements and news.
Moreover, as we shall explain below, we use the trademarks filed at USPTO to proxy for advertising efforts.
Typically, the day when a firm files for a trademark does not coincide with the day in which a new advertising
campaign starts. From our interviews with managers of the two companies, it emerges that the delay period
between the filing and the campaign is approximately one week. Thus a monthly scale is likely to overcome this
potential problem.
11
We therefore make a step further and estimate the following equation:
tititti SDv ,,210, )ln()ln()ln( κθφφφ +∆+++= (2)
where Dt is total demand of carbonated soft drinks at period t and Si,t is firm i’s market share in period
t. As one could easily note, equation [2] is inefficient since Dt and Si,t are endogenous variables that
produce heteroscedastic residuals. We show the results only to provide qualitative information on the
effect of total demand and firm i’s market share on its market value. Moreover, this estimation cannot
directly test our Hypotheses on rival product introductions and advertising efforts.
Thus, as a final step we propose a Generalized Method of Moments (GMM) estimation of [2]
in which Dt and Si,t are instrumented with new product introductions (Pit, Pjt) and advertising efforts
(Ait, Ajt) of firm i and its rival.
This estimation not only allows us to test if the effects of our core variables are similar to [1],
but also how these covariates affect separately total demand Dt and firm i’s market share Si,t. This is
important in order to understand which of the different effects discussed in the hypotheses is more
likely to prevail. A GMM estimation is well suited because it controls for potential correlation across
residuals and for possible heteroscedasticity. Thus, the estimation model will be:
+∆+++++=
+∆+++++=
+∆+++=
titjtitjtiti
titjtitjtit
tititti
AAPPS
AAPPD
SDv
,,4,3,2,10,
,,4,3,2,10
,,210,
)ln()ln()ln()ln(
)ln()ln()ln()ln(
)ln()ln(
ζηϑϑϑϑϑ
θιψψψψψ
κθβββ
(3)
4.2. Dependent Variable
As dependent variable, we employ a classical measure of firm financial-market value: the Tobin’s q.
Tobin’s q is a widely used indicator of firm value in the economic and management research,
especially to measure intangible assets (Dowell et al. 2000; Hall et al. 2005). Tobin’s q has been
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widely used in the literature that relates a firm’s innovation activity to its financial performance.
Tobin’s q is defined as the firm’s financial-market value per dollar of replacement costs of tangible
assets. Firm financial-market value equals to outstanding shares times share price plus book value of
long-term debt and net current liabilities. In a monthly scale, we take both the monthly averages of the
daily closing share prices and that of the outstanding shares. Replacement cost of tangible assets is the
sum of book value of inventory and net value of physical plant and equipment. Data are from SEC
filings. Since accounting data change every four months only, we use linear interpolation to assign the
change to each month. Precisely, if we observe that the replacement cost increases by USD 20
between two quarters, we count for each month an increase of USD 5. Although this might sound like
a limitation, one needs to keep in mind that more than 90% of the variability of Tobin’s q is due to the
variability of the numerator, not the denominator.
4.3. Variables of theoretical interest
The two variables of theoretical interest are new product introductions and advertising efforts by firm
i’s rival. We proxy these two variables with the announcements of new product introductions and the
trademarks filed at the US Patent and Trademarks Office, respectively.
Product introduction data come from Infotrac’s Promt database that, from a large set of trade
journals, magazines and other specialized press, reports several categories of events like product
introductions classified by SIC codes. This database is the new version of the old Predicast database
that has been used extensively in the literature (e.g. Pennings and Harianto 1992). We searched for all
press articles that are classified as a ’Product announcement’, a ’New product release’ and a ’Product
introduction’ for Coca-Cola and Pepsi between January 1999 and December 2003. Then, from each of
these articles, we extracted the date of product introduction (month and year) and we used the text and
the precise SIC code of the article to select only those products introduced in the CSD niche.3 We then
create the variable PRODUCTj,t that represents the number of product introductions announced by firm
3 Precisely, we excluded tropical/milky and other types of juices, tea/coffee/infusions, water,
energetic/vitamin/sport drinks and yoghurts.
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i’s rival in a given month. By and large, product announcements can be attributed to two categories: i)
new products (i.e. Cherry Mountain Dew, Lime Diet Coke, etc.), and ii) new packages, cans or bottles
of existing products (i.e. limited edition, silver-colored plastic 2 litre bottle, etc.).
Trademarks are combinations of ‘words, phrases, symbols or designs that identify and
distinguish the source of the goods or services of one party from those of others’ (USPTO
Documentation, http://tess.uspto.gov). Firms can register as a trademark a new name, a jingle or a
slogan, a new image or a logo (i.e. ‘can’t leave without it’).4
An interesting example that better explains the role of trademarks as a measure of advertising
efforts in CSD is the following. In 2004, the 25th of October, Coca-Cola filed for the trademark make
it real, that the US Patent and Trademark Office granted with the number 78,505,276. Randy Ransom,
senior vice-president for Coca-Cola trademark marketing at Coca-Cola North America described the
new campaign in this terms: “The new campaign, called make it real, attempts to take the message of
the Atlanta beverage company’s two-year-old ’Coca-Cola Real’ campaign to a new level [. . . ] Many
industry observers applauded the Real campaign for making strides in connecting with younger
consumers” (Wall Street Journal 2005).
We downloaded all the trademarks whose owner is Coca-Cola or Pepsi and with a filing date
between January 1999 and December 2003. Looking at the good and service description, we selected
only the CSD-related trademarks. Similarly to product introductions, we created the variable
TRADEMARK j,t that is the monthly number of trademarks filed by the rival firm.5
It is worth noting that the two firms use to concentrate advertising in different periods of the year:
Coca-Cola during Christmas holidays and Pepsi during summer holidays. Indeed, the correlation
between the time series of Coca-Cola and Pepsi trademarks equals to 0.126, not significant at 10%
level. Note also the variation especially of the trademarks variables in the Table 1. This rich variation
4 The US trademark owners pay different types of fees for each class of goods/services for which a trademark is
registered, and they have to prove periodically that they are using the trademark in the US market. The front
page of the trademark provides useful information - e.g. the owner’s name and address, the date when a complete
application was received by the USPTO (filing date), and the good and services description. 5 The good and service description contains a written explanation that clearly identifies the nature of the goods
and/or services as set forth in the application or registration.
14
is difficult to extract from accounting data that in the period 1999-2003 show for the two firms an
average growth rate of advertising expenses of only 1.1%, with a standard deviation of 0.8%.
4.4. Controls
As exogenous control variables, we employ firm i’s product introductions and trademarks in the
carbonated niche, PRODUCTi,t and TRADEMARKi,t. As we also mentioned in the theory section there is a
direct effect of a firm’s product and advertising efforts on its financial-market value.
We construct also a firm dummy variable that takes the value of 1 for Pepsi and 0 for Coca-
Cola. The firm dummy aims to proxy for ’the fixed effect of attraction of the brand’ (Russell and
Kamakura 1994).
Month dummies are inserted to control for possible seasonal variations in the potential
demand.
From the Consumer Expenditure Survey of the Bureau of Labour Statistics, we obtained the
US annual consumer expenditure for food and beverages products (in USD millions). This variable
proxies for household income effects that might affect total potential demand for soft drinks
(FOODEXPENDITUREt).
Finally, we have two endogenous controls that are total demand Dt and firm i’s market share
Si,t. From Beverage Digest (www.beverage-digest.com) we obtain the annual number of 192-oz cases
sold (one case equals to 1.5 gallons). We divide this number by 12 to obtain our proxy for Dt
(DEMANDt). With the same data, we construct the proxy for Si,t. dividing the number of cases sold by
each firm by the total number of cases sold in a month (MARKETSHAREi,t). Table 1 shows the basic
descriptive statistics.
[Insert Table 1 about here]
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5. Results
5.1. Robust OLS
The results of robust OLS estimations are reported in Table 2. This regression estimates Equation [1].
The scale is logarithmic. Model 1 omits the core covariates, showing only the baseline model with all
control variables. Model 2, 3, and 4 progressively add our covariates of interest.
The first result is that PRODUCTj,t has a negative impact on firm i’ market value, that is, the
higher the rate of product introduction in a given month for Coca-Cola (Pepsi), the less will be Pepsi
(Coca-Cola) Tobin’s q. This suggests that product introduction has a strong ‘business stealing’ effect
or that the impact on total demand is rather modest.
On the other hand, TRADEMARK j,t positively impacts firm i’s market value, that is, the higher
the number of trademarks registered by Coca-Cola (Pepsi) in a given month, the larger will be Pepsi
(Coca-Cola) Tobin’s q. This finding suggests that the type of advertising protected through trademarks
is more likely to be generic rather than brand advertising. In fact, according to Hypothesis 2, firm i’s
market value can only increase with rival advertising efforts if the effect is mostly channelled through
an increment in total demand. Put differently, the business stealing effect of trademarked advertising
seems to be modest.
[Insert Table 2 about here]
It is possible to gain additional insights from considering the following experiment: using Model 4 and
all other variables held at their mean values, if firm j increases the monthly average number of product
introductions from 1 to 11 (the observed maximum), firm i’s Tobin’s q decreases by more than 60%.
Instead, a change in firm j’s average monthly trademarks from 1 to 29 enhances firm i’s Tobin’s q by
more than 30%.
As expected, PRODUCTi,t and TRADEMARK i,t show a positive and significant coefficient,
confirming that a firm’s efforts in product innovation and advertising increase its market value.
16
It is also worth comparing the magnitude of the own and rival’s effects. If a firm introduces
new products, it increases its Tobin’s q with the same intensity than it reduces the rival’s market value
(0.824 vs 0.887 from Model 4). If the firm files new trademarks, it increases its and the rival’s Tobin’s
q by about the same amount (1.113 vs 1.145). Thus, the market interprets that product introductions
give raise to quite a perfect shift of market shares from one firm to the other, while advertising efforts
generate an overall boost in profitability that is evenly shared.
Finally, FOODEXPENDITUREt has a positive and significant impact on firm i’s market value,
while Pepsi has, other things equal, a lower Tobin’s q.
5.2. GMM estimation
Table 3 shows the results of the simple OLS estimation of Equation [2].
[Insert Table 3 about here]
As expected, both DEMANDt and MARKETSHAREi,t produce a positive impact on firm i’s market value.
However, this estimation has only a qualitative interpretation, due to its inner inefficient feature.
The next step is to estimate Equation [3], using firm i and firm j’s efforts in product
introductions and advertising as exogenous instruments influencing DEMANDt and MARKETSHAREi,t
(all other control variables are also included as instruments). Results are reported in Table 4.
[Insert Table 4 about here]
First, Table 4 highlights that the main effects of DEMANDt and MARKETSHAREi,t are confirmed.
Second and far more interesting, we can sort out how PRODUCTj,t and TRADEMARKj,t impact firm i’s
financial-market value. MARKETSHAREi,t does not seem to depend on the advertising efforts of neither
firm i nor firm j. Instead, it is directly influenced by the product releases of the two firms, so that
PRODUCTj,t has a negative and PRODUCTi,t a positive effect. By contrast, total demand only depends on
17
advertising efforts. Both TRADEMARKj,t and TRADEMARKi,t show a positive effect on DEMANDt,
whereas product introductions do not have a significant effect.
Therefore, the GMM estimation not only does it confirm our main finding that rival advertising
increases a firm’s financial-market value, while rival product introduction decreases it, but it also
suggests that these two dimensions of the marketing mix act through different channels. Advertising
boosts total industry demand, so that rival efforts have a positive spillover on a firm’s market value.
Product introduction is an aggressive tool that directly affects the distribution of market shares,
implying a negative impact.
5.3. Robustness checks
To validate our analysis, we perform some robustness checks. We address the presence of potential
endogeneity due to autoregressive trends that could bias our findings. Endogeneity could arise from
different sources. The efforts the firms exert in product innovation or advertising are likely to be the
result of a chosen strategy. So, it is possible that both product and trademark introductions follow a
common firm’s strategy that also encompasses a response to the moves of its direct rival. Moreover,
given the lag at which firms observe success or failure of their strategies, the actual decisions could be
influenced by past actions and manoeuvres. Additionally, measurement errors in our dependent
variables might produce endogeneity, and thus bias our estimates. To tackle this problem, we resort to
instrumental variable techniques.
Specifically, we use as instruments for the number of product introductions and trademarks the
lagged variables (one month lag) of firm i’s and firm j’s product introductions and trademarks. For
example, PRODUCTj,t is explained with PRODUCTj,t-1, PRODUCTi,t-1, TRADEMARKj,t-1, TRADEMARKi,t-1,
plus all other exogenous variables.
In Table 5, Model 1 presents the results of the GMM estimation. As a matter of facts, results
are similar. Overall, GMM estimation with autoregressive instruments does not substantially alter the
main results.
18
[Insert Table 5 about here]
We also replicate the regression with a different measure of firm financial-market value: the
unexpected cumulate average excess of stock market returns (CAR). CAR is proposed in this study as
a robustness check, since it is usually employed in event studies on a daily base. In fact, even if the
interpretation of a monthly CAR is far from its pure financial meaning, we think that our hypotheses
could gain additional support from this test. To obtain a monthly CAR we follow a consolidated
procedure (Chaney et al. 1991). For each firm we calculate the realized returns as RRi,t = (Pi,t+di,t−Pi,t-
1)/Pi,t-1 where Pi,t is the closing daily price and di,t is the eventual dividend paid. Then, we predict RRi,t
using the estimated parameters of the following equation: ERRi,t = αi + βiSPi,t, where SPi,t is the
composed Standard and Poor’s 500 index. For each ERRi,t, the sample period employed for the
estimation of αi and βi is equivalent to 200 days before the day t. We then calculate the rough
unexpected daily return as RCARi,t = RRi,t − ERRi,t and finally we obtain the unexpected cumulate
average excess of stock market returns as a moving average in a 3 day time window of RCARi,t. Since
we have monthly data, we take the monthly average of RCARi,t for each firm. Stock market prices and
indexes are from Yahoo!Finance and corporate websites. Model 2 of Table 5 shows the results that
hold un-changed in terms of sign and significance for our core covariates.
We have performed some other regressions that we do not show here but are available upon
request. For example, results hold unchanged when we use the quarter rather than the month as a time
unit of observation, and when we introduce multiplicative effects among our core variables, which are
not statistically significant.
6. Conclusions
Our primary aim in this article was to provide empirical evidence on how the financial-market value of
a firm reacts to rival moves along two dimensions of the marketing mix: product introductions and
advertising efforts.
19
In so doing, we contributed to two rising research trajectories that investigate i) how non-price
moves impact on a firm market value (Bayus et al. 2003; Azoulay 2002; Hui 2004; Pauwels et al.
2004; Srinivasan et al. 2006) and ii) how other firms’ actions influence this value (Das, Sen and
Sengupta 1998; Silverman and McGahan 2006).
We tackle this issue by focusing on the efforts in product introduction and advertising of
Coca-Cola and Pepsi in the Carbonated Soft Drink market in a period characterized by price stability
(1999-2003). Our study generates two main findings. First, we show that Coca-Cola (Pepsi) new
product introductions are associated with a decrease of Pepsi (Coca-Cola)’s Tobin’s q, while Coca-
Cola (Pepsi) advertising efforts have a positive significant effect on Pepsi (Coca-Cola)’s financial-
market value. Overall, the evidence seems to suggest that while product innovation tends to be an
aggressive competitive manouvre, advertising is a more accommodating tool.
Second, our findings highlight that product introduction and advertising affect a firm’s
financial-market value through different channels: Advertising acts mostly on total demand, while
product releases affect mostly the distribution of market shares.
Our conclusions include several implications for investors, managers and policy makers. For
investors, our results make clear that, especially in oligopolistic markets, the financial value of a firm
is sensibly affected by the actions of its competitors. Financial models that understimate the impacts of
rival actions, could indeed produce bias forecasts of firm potentialities. We think that this represents
an important lens to measure a firm financial value, especially for shareholders who want to assess the
performance of the strategies proposed by the board of managers.
The previous argument implies that a necessary condition for managers to elaborate correct
strategies is to single out the different impulses that come from the surrounding enviroment, especially
in terms of competitors’ moves. Advertising and new product introductions are two major sources of
firm investments and, thus, key areas of managerial decisions. In our view, managers not only have to
understand the impact of a particular move, but also the channels through which this move acts. We
show that in the CSD market advertising increases a firm’s and a rival’s financial-market value by
increasing total demand, while new product releases steal market shares. Therefore, the correct timing
20
and alternation of these two moves, adapted also to the observed rival moves, could increase the value
of a firm in an important way. The very fact that at the end of the year 2005 Pepsi overtakes Coca-
Cola in terms of market capitalization for the first time in more than a century of history has been
interpreted as a “humiliating reversal” by the Atlanta-based company shareholders (Economist 2005).
Policy makers and antitrust analysts could benefit from this study by noting that some of the
firms’ investments could have a more collusive effect. We claim that more detailed investigations
particularly on the role of advertising in oligopolistic industries could shed new light of the extent to
which promotion is used to increase entry barriers and to consolidate dominant position.
These final conjectures open up several extensions that we could not address in this work but
are avenues for future research. In this respect, we think the most intriguing are: i) the relationship
between efforts in advertising, in product innovation and the size of churn demand; ii) the patterns of a
firm response functions – both for advertising and product releases.
Acknowledgements
We would like to thank Kai-Lung Hui, Nora Lado, Marcello Mariani, Marco Seregni, Anna Torres and
seminar participants at the 2nd EIASM Co-opetition Conference (Bocconi University) and Universidad Carlos
III de Madrid for comments and suggestions on an earlier draft. The usual disclaimer applies.
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Table 1: Descriptive Statistics
Variable Obs Mean Std.Dev. Min Max
TOBIN’S Qi,t 120 3.88 2.72 1.68 6.31
PRODOCTj,t 120 1.325 1.572 0 11
TRADEMARKj,t 120 2.675 4.203 0 29
FOODEXPENDITUREt 120 437.08 10.915 419.25 447.916
MONTHDUMMY 120 0.83 0.277 0 1
FIRMDUMMY 120 0.5 0.52 0 1
DEMANDt 120 631.20 6.302 624.750 640.625
MARKETSHAREi,t 120 0.5 0.083 0.415 0.584
26
Table 2: OLS Robust Regression, estimation of Equation [1], Y=Tobin’s qi,t
Model1 Model2 Model3 Model4
PRODUCTj,t -0.851**
(0.384)
-0.887**
(0.341)
TRADEMARKj,t 1.103**
(0.339)
1.113**
(0.331)
Controls
PRODUCTi,t 0.608*
(0.331)
0.908*
(0.480)
0.524*
(0.333)
0.824*
(0.456)
TRADEMARKi,t 1.102**
(0.432)
1.068**
(0.333)
1.140**
(0.335)
1.145**
(0.343)
FOODEXPENDITUREt 0.048**
(0.016)
0.050**
(0.018)
0.043**
(0.012)
0.044**
(0.012)
FIRMDUMMY -0.263**
(0.046)
-2.823**
(0.456)
-1.762**
(0.531)
-2.101**
(0.519)
MONTHDUMMY Yes Yes Yes Yes
CONSTANT 2.243**
(0.378)
2.246**
(0.462)
2.294**
(0.685)
2.834**
(0.687)
R2 0.231 0.299 0.293 0.322
OBS. 120 120 120 120
Notes: i) Heteroskedastic consistent standard errors in parenthesis. ii) **significance 0.05; * 0.10
27
Table 3: OLS Robust Regression, estimation of Equation [2], Y=Tobin’s qi,t
Model 1 Model 2 Model 3
DEMANDt 3.915**
(0.745)
3.867**
(0.821)
MARKETSHAREi,t 11.103**
(5.339)
13.252**
(4.331)
Controls
FOODEXPENDITUREt 0.750**
(0.051)
0.643**
(0.061)
0.751**
(0.055)
FIRMDUMMY -3.263**
(1.046)
-2.823**
(1.024)
-4.232**
(1.387)
MONTHDUMMY Yes Yes Yes
CONSTANT 2.849**
(0.845)
3.051**
(0.775)
3.111**
(0.949)
R2 0.493 0.502 0.653
OBS. 120 120 120
Notes: i) Heteroskedastic consistent standard errors in parenthesis. ii) **significance 0.05; * 0.10
28
Table 4: GMM Regression, estimation of Equation [3]
Model 1 Model 2 Model 3
Y=Tobin’s qi,t
DEMANDt 16.738**
(1.273)
15.795**
(6.608)
15.795**
(7.608)
MARKETSHAREi,t 7.892**
(3.971)
4.495**
(1.808)
8.248**
(3.688)
CONSTANT 10.508**
(3.740)
10.204**
(3.335)
10.249**
(4.749)
Y=MarketShare
PRODUCTj,t -0.042**
(0.009)
-0.040**
(0.009)
TRADEMARKj,t 0.504
(0.954)
0.344
(0.651)
PRODUCTi,t 0.051**
(0.010)
0.050**
(0.010)
TRADEMARKi,t 0.302
(0.938)
0.443
(0.657)
CONSTANT 0.487**
(0.018)
0.489**
(0.017)
Y=Demand
PRODUCTj,t 1.993
(1.549)
0.993
(0.909)
TRADEMARKj,t 0.600**
(0.002)
0.053**
(0.008)
PRODUCTi,t 2.700
(1.855)
0.600
(0.862)
TRADEMARKi,t 1.233**
(0.573)
0.032**
(0.008)
CONSTANT 6.263**
(1.242)
6.283**
(1.248)
MONTHDUMMY
FIRMDUMMY
FOODEXPENDITUREt
Always inserted in all equations
R2 0.893 0.835 0.895
OBS. 120 120 120
Notes: i) Heteroskedastic consistent standard errors in parenthesis. ii) **significance 0.05; * 0.10
29
Table 5: Robustness Checks
Y=Tobin’s qi,t Y=RCARi,t
PRODUCTj,t -0.010**
(0.003)
-0.0039**
(0.0017)
TRADEMARKRIVALj,t 0.011**
(0.002)
0.0065**
(0.0024)
Controls
PRODUCTi,t 0.007*
(0.004)
0.0035**
(0.0017)
TRADEMARKi,t 0.010**
(0.003)
0.0012*
(0.0007)
FOODEXPENDITUREt 0.011
(0.012)
0.004
(0.005)
FIRMDUMMY -0.019**
(0.004)
0.004
(0.006)
MONTHDUMMY Yes
CONSTANT 2.243**
(0.378)
-0.006
(0.005)
R2 0.308 0.06
OBS. 118 120
Notes: i) Model 1 GMM estimation; ii) Model 2 uses CAR as dependent variable. iii) Standard error in
parentheses. Standard Errors computed from heteroscedastic-consistent matrix (Robust–
White). iv) ** significance 0.05; * 0.10.
30
APPENDIX
Let vit be the market value of firm i at time t, that is the net present value of its future stream of profits
∑∞
= +
−=
0 )1(tt
ititititit
r
xcxpv where p is the product price, x the number of goods sold, c constant marginal
cost and r the discount rate. Let us assume that p, c and r are constant over time, a fair assumption for
the Carbonated Soft Drink market. Indeed, in the period 1999-2003, the cost of good sold for the two
firms increased only by 4.5%. Therefore, the market value solves as )()( itit xEr
p
r
cv +
−= . Assume
also that the number of goods sold by the firm i follows a Poisson process !
)(~
x
Tex
xT
it
λλ−
. The λ
parameter, that in a Poisson process is the probability that an event occur in a unit of time, could be
interpreted as firm i‘s market share (Si,t), that is the probability that a consumer will buy the brand i.
The parameter T, the total period of time elapsed, could be interpreted as total demand (Dt) (see also
Russell and Kamakura 1994). Therefore, the expected value of x equals to titit DSxE =)( . This means
that firm i’s market value reads ittit SDr
p
r
cv )( +
−= that in logarithm scale is
)ln()ln()ln()ln( ittit SDr
pcv ++
+−= , very similar to our equation [2].