ABSTRACT
RICHE, STEPHANIE MORGAN. Three Essays in Trade and Health. (Under the direction of Barry K. Goodwin and Ivan Kandilov.)
The first piece of research in this dissertation involves an analysis of the price impact
of an embargo. I conduct an event study of the United States’ four-day soybean export
embargo and subsequent licensing in 1973. I follow an econometric model similar to that
of a difference-in-differences (DID) model. First, I use a relative price of a substitute
good method to estimate the price impact of the event. I compare the prices of soybeans
to those of substitutes not impacted by this embargo. I also look at domestic prices
ver-sus world prices in a similar fashion. I apply time-series analysis techniques appropriate
for nonstationary and potentially cointegrated price series in measuring the impacts of
the embargo on equilibrium price relationships. The“event study” analysis begins with
an analysis of long-run structural breaks at known and unknown joint points.
Implica-tions for the substantial rise in the prominence of Brazilian soybean exports and the
concomitant adjustments realized in the United States’ export market are discussed.
In Chapter Three, I explore international real interest rates. The real interest rate
parity (RIP) hypothesis is one of the tenets of international economics. Due to the
devel-opment of financial markets over the past few decades, it is likely that capital markets
are more integrated now than in the past. I analyze the dynamic linkages between real
ex ante interest rates using nonlinear models. I, first, use a threshold model to analyze
the dynamic linkages of various countries’ ex ante real interest rates. To begin, I consider
(1998) respectively. Next, I develop copula-based models that consider the joint
distri-bution of different national interest rates. This allows attention to be given to the nature
of the jointness or correlation between these interest rates. I allow for the correlation
to be state-dependent and depend on market conditions at any point in time. This is
analogous to the regime-switches in the above models. Copula models use a copula to tie
together two marginal probability functions that may (or may not) be related to one
an-other. The copula method offers an alternative approach to representing the multivariate
distribution in terms of its dependent marginals. In this paper, I utilize many nonlinear
and nonparametric techniques for assessing the dynamic linkages in international interest
rates. These methods show the level of integration within the market and stress the level
to which policy makers have the ability to independently influence their home country’s
interest rate.
Finally, in Chapter Four, I examine the relationship between Methicillin-resistant
Staphylococcus aureus (MRSA) and swine farms. In recent years, there have been
nu-merous headlines about ”Superbugs.” These infections exhibit antibiotic resistance and
are increasingly difficult to treat. In the decades following its discovery, hospital-acquired
MRSA (HA-MRSA) strains have become resistant to a myriad of commonly used
an-tibiotics. In the last twenty years, many people have been increasingly diagnosed with
MRSA without having had contact with a hospital setting. These strains are known as
community-acquired MRSA (CA-MRSA). Currently, MRSA kills more people each year
than AIDS. MRSA can also be spread between humans and animals from close contact,
such as in a farm setting. Specifically, in Canada, 20 percent of swine farm workers, 25
of MRSA. In all countries with MRSA colonization in swine farms, the workers on those
farms and their families are found to test positive in large proportions.The goal of this
paper is to test whether there is a link between the increasing presence of MRSA on
swine farms with the uptick in CA-MRSA using North Carolina hospital discharge data
in logistic regression models and county level data using count and fractional models. The
results of this paper show whether a person’s proximity to swine farms and
concentra-tion of said swine farms is related to their likelihood of contracting CA-MRSA. This has
many implications for public health officials. With the increasing numbers of CA-MRSA
infections and the high number of people dying from MRSA infections, officials are eager
©Copyright 2014 by Stephanie Morgan Riche
Three Essays in Trade and Health
by
Stephanie Morgan Riche
A dissertation submitted to the Graduate Faculty of North Carolina State University
in partial fulfillment of the requirements for the Degree of
Doctor of Philosophy
Economics
Raleigh, North Carolina
2014
APPROVED BY:
Nicholas Piggott Mehmet Caner
Barry K. Goodwin
Co-chair of Advisory Committee
Ivan Kandilov
DEDICATION
This dissertation is dedicated to my parents, as well as Schatzi and Toby for their
un-conditional love.
BIOGRAPHY
Stephanie was born in Monrovia, California on July 26, 1985. Her family moved to
Orlando, Florida when she was quite young where Stephanie graduated from high school
in 2002 in just three years, graduating in the top of her class. She continued on to the
University of Florida on scholarship. She graduated cum laude in 2005.
After high school, Stephanie taught high school mathematics at Winter Spring High
School as a long-term substitute. After the term was over, Stephanie worked for a custom
home builder in Winter Park, Florida as at the Assistant Director of Operations. Shortly
thereafter, she applied and enrolled in Rollins College’s Crummer School of Management
for an M.B.A. with concentrations in international business and finance. During this
degree, she fell in love with economics and enrolled in additional economics courses at
University of Central Florida.
In the fall of 2008, Stephanie enrolled at North Carolina State University to
pur-sue a Ph.D. in economics. Her fields of specialization are International Trade, Applied
Econometrics, Health Economics and Agricultural and Resource Economics. Her studies
ACKNOWLEDGEMENTS
Over the tenure of my Ph.D. I have received amazing support, guidance and advice from
so many people I could never acknowledge all properly. This is a poor substitute, but I
will attempt to distribute my gratitude here.
First, I would like to thank my advisor and committee co-chair, Dr. Barry Goodwin.
You have continually supported and guided me through the dissertation process. Without
your encouragement and belief in me, I would not be submitting this dissertation today.
Thank you Dr. Goodwin, for all your time, energy, patience and effort over these past
few years. You have been a great mentor. I hope to continue to collaborate with you in
the future.
Second, I would like to thank my co-chair Dr. Ivan Kandilov. Your enthusiasm for
eco-nomics is contagious. I always came out of meetings with you amazed at your knowledge
of what at times seemed like an infinite spectrum of topics. Your advice was indispensable
during the entire dissertation process. Any issue I ran in to you always were willing to
help, even when I stopped by while you ate lunch or were trying to leave the office.
Dr. Nick Piggot has been an amazing resource this past year. You have incredible
patience and was genuinely invested in my success. Dr. Piggott went above and beyond
helping me prepare for the job market and I will forever be indebted to you for the time
you have invested in me.
Next, Dr. Mehmet Caner has been an incredible resource throughout my entire Ph.D.
The training I received in your econometrics courses is invaluable. Thank you for agreeing
to serve on my committee. I thoroughly have enjoyed getting to know you over the past
few years and will never forget our conversations dissecting the plot of Lost.
To Dr. Melinda Morrill, while you did not sit on my committee, I would like to thank
you for all of your help during my Ph.D. You have given me more advice than you realize.
From helping me narrow my research interests, to career advice, you have always been a
person I trust and turn to. Thank you for all your help.
My parents, David and Mary Riche, have provided me with limitless support, love
and patience while I completed this dissertation. I appreciate all of their understand for
the time that I had to spend away from the family during holidays and other major
events. The care packages (consisting of mostly food at this point) were amazing and
always came at the exact moment I was at my highest stress level. You two have always
supported me through this insanely long journey, and I promise this is my last degree.
Thank you and I love you both.
Finally, I would like to thank all of the other faculty members at North Carolina State
University that have helped me over the years, be in during a course, in a hallway or
in a seminar presentation. All of you have helped me become who I am today and I am
forever indebted. Thank you Dr. Tamah Morant, for all of your guidance from start to
TABLE OF CONTENTS
LIST OF TABLES . . . vii
LIST OF FIGURES . . . viii
Chapter 1 Introduction . . . 1
1.1 Price Impact of an Embargo - The 1973 Soybean Embargo in the United States . . . 1
1.2 Modeling Nonlinear Dynamic Linkages Among Real Interest Rates . . . . 3
1.3 A Spatial Analysis of MRSA and Livestock Farms . . . 5
Chapter 2 The Price Impact of an Embargo: The 1973 Soybean Em-bargo in the United States . . . 7
2.1 Introduction . . . 7
2.2 Background and Methodology . . . 11
2.3 Data and Results . . . 12
2.4 Discussion . . . 19
2.5 Concluding Remarks . . . 22
Chapter 3 Modeling Nonlinear Dynamic Linkages Among Real Interest Rates . . . 44
3.1 Background . . . 44
3.2 Methodology . . . 46
3.3 Results . . . 53
3.4 Conclusion . . . 61
Chapter 4 A Spatial Analysis of MRSA and Livestock . . . 89
4.1 Background . . . 89
4.2 Data and Methodology . . . 91
4.3 Results . . . 96
4.4 Conclusion . . . 100
Chapter 5 Conclusions . . . 124
Bibliography . . . 128
LIST OF TABLES
Table 2.1 Cointegration Tests on Daily Prices . . . 24
Table 2.2 Determination of Number of Structural Breaks . . . 25
Table 2.3 Pre-Embargo Vector Error Correction Model Estimates For Daily Prices . . . 26
Table 2.4 Cointegration Tests for Monthly Domestic and Rotterdam Soybean Prices . . . 27
Table 2.5 Pre-Embargo Vector Error Correction Model Estimates for Monthly Domestic and Rotterdam Soybean Prices . . . 28
Table 2.6 Cointegration Tests for Monthly Soybean and Corn Prices . . . 29
Table 2.7 Pre-Embargo Vector Error Correction Model Estimates for Monthly Soybean and Corn Prices . . . 30
Table 3.1 Descriptive Statistics - Pre Euro . . . 65
Table 3.2 Descriptive Statistics - Post Euro . . . 66
Table 3.3 Pre Euro Results from Frankel Method Estimation of (iτ1−iτ2)t= α+β(iτ1−iτ2) t−1+ut . . . 67
Table 3.4 Post Euro Results from Frankel Method Estimation of (iτ1−iτ2)t= α+β(iτ1−iτ2)t−1+ut . . . 68
Table 3.5 Pre Euro AR and TAR Estimates . . . 69
Table 3.6 Pre Euro AR and TAR Estimates . . . 70
Table 3.7 Post Euro AR and TAR Estimates . . . 71
Table 3.8 Post Euro AR and TAR Estimates . . . 72
Table 3.9 Pre Euro Markov Switching Model Estimates . . . 73
Table 3.10 Post Euro Markov Switching Model Estimates . . . 74
Table 3.11 Pre Euro Copula Parameter Estimates (With Empirical Marginals) C(∆(ri t−r j t),(rit−1−r j t−1)) . . . 75
Table 3.12 Post Euro Copula Parameter Estimates (With Empirical Marginals) C(∆(ri t−r j t),(rit−1−r j t−1)) . . . 76
Table 4.1 Descriptive Statistics - All Patient Data . . . 103
Table 4.2 Descriptive Statistics - All County Data . . . 104
Table 4.3 Individual Level Analysis - All Years . . . 105
Table 4.4 Individual Level Analysis - 2007 - 2011 Separately . . . 106
Table 4.5 County Regression Results - All Years . . . 107
LIST OF FIGURES
Figure 2.1 Daily Log Prices Before Event . . . 31
Figure 2.2 Daily Log Relative Prices with Break . . . 32
Figure 2.3 Forecasted Daily Prices from VECM with Observed Prices . . . . 33
Figure 2.4 Cumulative Abnormal Returns for Log(Soy) . . . 34
Figure 2.5 Cumulative Abnormal Returns for Log(Corn) . . . 35
Figure 2.6 Monthly Prices of Domestic Soy and Export Soy . . . 36
Figure 2.7 Monthly Log Relative Prices of Domestic Soy and Export Soy . . 37
Figure 2.8 Forecasted Monthly Prices from VECM with Observed Prices
(Do-mestic and Exported Soybeans) . . . 38
Figure 2.9 Cumulative Abnormal Returns for Monthly Domestic Log Soybean
Prices . . . 39 Figure 2.10 Cumulative Abnormal Returns for Monthly World Log Soybean
Prices . . . 40
Figure 2.11 Monthly Log Prices of Soy and Corn . . . 41
Figure 2.12 Monthly Log Relative Prices of Soy and Corn . . . 42
Figure 2.13 Forecasted Monthly Prices from VECM with Observed Prices (Soy-beans and Corn) . . . 43
Figure 3.1 Pre Euro Ex Ante Expected Real Interest Rates and Ex Post Real
Interest Rates . . . 77
Figure 3.2 Pre Euro Distributions and Kernel Densities for Real Interest Rate
Differentials . . . 78
Figure 3.3 Pre Euro Distributions and Kernel Densities for First-Differenced
Real Interest Rate Differentials . . . 79
Figure 3.4 Pre Euro ECM Copulas . . . 80
Figure 3.5 Pre Euro Estimated Copula Function Mean Relationships (From
Nonparametric Marginals):C(∆(rti−rjt),(rti−1−rjt−1)) . . . 81
Figure 3.6 Derivatives of Standard Linear VEC Models and Copula Models . 82
Figure 3.7 Pre Euro Ex Ante Expected Real Interest Rates and Ex Post Real
Interest Rates . . . 83 Figure 3.8 Post Euro Distributions and Kernel Densities for Real Interest Rate
Differentials . . . 84
Figure 3.9 Post Euro Distributions and Kernel Densities for First-Differenced
Real Interest Rate Differentials . . . 85
Figure 3.10 Post Euro ECM Copulas . . . 86
Figure 3.11 Post Euro Estimated Copula Function Mean Relationships (From
Nonparametric Marginals):C(∆(rti−rjt),(rti−1−rjt−1)) . . . 87
Figure 3.12 Derivatives of Standard Linear VEC Models and Copula Models . 88 Figure 4.1 Number of Swine Farms by County in North Carolina . . . 109
Figure 4.2 Number of Hogs by County in North Carolina . . . 110
Figure 4.3 Concentration of Swine Farms by County in North Carolina . . . 111
Figure 4.4 All Years - MRSA Infections by County in North Carolina . . . . 112
Figure 4.5 2007 MRSA Infections by County in North Carolina . . . 113
Figure 4.6 2008 MRSA Infections by County in North Carolina . . . 114
Figure 4.7 2009 MRSA Infections by County in North Carolina . . . 115
Figure 4.8 2010 MRSA Infections by County in North Carolina . . . 116
Figure 4.9 2011 MRSA Infections by County in North Carolina . . . 117
Figure 4.10 All Years - MRSA Incidence Rate per 100,000 People by County in North Carolina . . . 118
Figure 4.11 2007 MRSA Incidence Rate per 100,000 People by County in North Carolina . . . 119
Figure 4.12 2008 MRSA Incidence Rate per 100,000 People by County in North Carolina . . . 120
Figure 4.13 2009 MRSA Incidence Rate per 100,000 People by County in North Carolina . . . 121
Figure 4.14 2010 MRSA Incidence Rate per 100,000 People by County in North Carolina . . . 122
Chapter 1
Introduction
The following dissertation is broken in to three chapters of work. Each chapter delves
into a separate topic. Below are brief descriptions of each chapter.
1.1
Price Impact of an Embargo - The 1973 Soybean
Embargo in the United States
In 1973, soybeans in the United States were in short supply and prices were increasing
rapidly. The failure of the Peruvian anchovy catch in 1972 dramatically decreased the
availability of high-protein feed for livestock and thereby greatly increased demand for
soybean meal, a high-protein substitute in livestock feed. In January 1973, the USDA
released restrictions on ”set-aside” cropland to help ease the tensions in the market and
increase the production of soybeans. To make matters worse, flooding hindered planting
in the spring of 1973. The U.S. dollar was devalued by approximately ten percent on
February 15, 1973, contributing to a marked increase in foreign demand for U.S. exports.
As an attempt to stabilize prices and ensure adequate domestic supply, the United States
implemented an export embargo of soybeans, cottonseed and their byproducts on June
27, 1973. The response from importers of these goods was so intense, the embargo was
swiftly lifted less than one week later, on July 2, 1973. The embargo was replaced with
an export-licensing system that was discontinued on September 21, 1973.
I follow a similar econometric model to that of Carter and Smith (2007) in their
analysis of the effect of a food scare due to genetically modified corn not approved for
human consumption being found in the food supply. As in Carter and Smith (2007), I use
a relative price of a substitute good method to estimate the price impact of the embargo.
I compare the prices of soybeans to those of a primary substitute, corn. Corn is a valid
substitute for soybeans due to the fact that they are production substitutes as well as
both are used primarily for animal feed. Also, corn was not affected by the embargo in
1973.
The Carter and Smith relative price of a substitute method exploits the time series
nature of the price of a commodity relative to the price of a substitute good to infer the
price impact of an event that did not impact the substitute good. This allows general
market fluctuations to be accounted for without the need for a formal structural supply
and demand model to be developed. To see the relative price dynamics of the two goods,
the relative price of the two goods must be stable prior to the event of interest. Once
shown stable, any change in the relative price implies a change in the underlying supply
and demand relationship. This allows for a direct estimation of the price impact of the
I apply time-series analysis techniques appropriate for nonstationary and potentially
cointegrated price series in measuring the impacts of the embargo on equilibrium price
relationships. The ”event study” analysis begins with an analysis of long-run structural
breaks at known and unknown joint points. To this end, I apply a conventional Chow
test for known structural breaks as well as the structural change tests of Hansen (1992),
Hansen (2001), Andrews, Lee and Ploberger (1996), Ploberger and Kramer (1992), and
Bai and Perron (1998). The latter tests are appropriate when the timing of a structural
break is unknown. In such a case, standard Chow-type tests have nonstandard
distribu-tions due to the presence of parameters that are unidentified under the null hypothesis of
no structural break. Upon confirming the presence of a statistically significant structural
break, I undertake estimation that identifies the multiple regimes corresponding to the
periods before and after the embargo.
1.2
Modeling Nonlinear Dynamic Linkages Among
Real Interest Rates
The real interest rate parity (RIP) hypothesis is one of the tenets of international
eco-nomics. Under RIP, well-functioning capital markets would allow for national real interest
rates to be tied to a world interest rate that is determined in the world credit market.
Due to the development of financial markets over the last few decades through removal
of capital controls and other investment barriers, it is likely that capital markets are
more integrated now than in the past. This is important for policy makers, especially in
countries that are small relative to the world credit market, because it ties a country’s
policy instrument to a world interest rate, thus limiting their abilities to effectively enact
policy independently.
I add to the literature by analyzing the dynamic linkages between real ex ante interest
rates using multivariate threshold models and copulas. First, I follow Frankel (1982) in
his calculation of ex ante real interest rates by deflating the nominal rate by a measure
of the ex ante inflation rate. I apply tests for nonstationarity and cointegration. Then,
I use a threshold model to analyze the dynamic linkages of various countries’ ex ante
real interest rates. To begin, I consider Markov switching models and threshold models
examined by Krolzig (1997) and Tsay (1998) respectively.
Finally, I develop copula-based models that consider the joint distribution of different
national interest rates. This allows attention to be given to the nature of the jointness or
correlation between these interest rates. I allow for the correlation to be state-dependent
and depend on market conditions at any point in time. This is analogous to the
regime-switches in the above models. Copula models use a copula to tie together two marginal
probability functions that may (or may not) be related to one another.
The copula method offers an alternative approach to representing the multivariate
distribution in terms of its dependent marginals. In the case of interest rate parity, the
degree of dependence that characterizes relationships in the tails of the distribution is
of particular relevance. The different types of copulas capture different aspects of this
behavior. To see which copula models fit best, I utilize sequential maximum likelihood
estimation of the copula model for each pair of interest rates. The optimal copula
func-tion(s) for each pair are then chosen using the minimized value of the Bayesin information
den-sities associated with higher-ordered, multivariate copula models of the elliptical and
Archimedean families as well as in vine copulas.
In this paper, I utilize many nonlinear and nonparametric techniques for assessing
the dynamic linkages in international interest rates. These methods show the level of
integration within the market and stress the level to which policy makers have the ability
to independently influence their home country’s interest rate.
1.3
A Spatial Analysis of MRSA and Livestock Farms
In recent years, there have been numerous headlines about ”Superbugs.” These infections
exhibit antibiotic resistance and are increasingly difficult to treat. Staphylococcus aureus
is a broad grouping of bacteria that tend to live inside the nose and on the skin. Most
of the time it is completely harmless and people don’t realize they are carrying what is
known as a colonization of the bacteria. This bacteria is easily spread from person to
person. Some strains of Staphylococcus aureus exhibit a resistance to a number of
an-tibiotics including methicillin. This is where Methicillin-resistant Staphylococcus aureus
(MRSA) gets its name. MRSA was first reported in 1961, shortly after methicillin was
introduced as treatment for strains that had developed a penicillin resistance. MRSA’s
origins were in hospitals, and it was mostly a hospital-acquired infection (HAI). In the
decades following its discovery, hospital-acquired MRSA (HA-MRSA) strains have
be-come resistant to a myriad of commonly used antibiotics. In the last twenty years, many
people have been increasingly diagnosed with MRSA without having had contact with
a hospital setting. These strains are known as community-acquired MRSA (CA-MRSA).
Currently, MRSA kills more people each year than AIDS.
MRSA can also be spread between humans and animals from close contact. This has
actually been found in some increasingly common strains, specifically ST398. The first
documented case of ST398 was in the early 2000s in the Netherlands. This is especially
noteworthy since the Dutch have incredibly low levels of HA-MRSA. This strain has been
found on many swine farms in Europe, Canada and the United States. Specifically, in
Canada, 20 percent of swine farm workers, 25 percent of pigs and 45 percent of farms
were reported to be colonized with various strains of MRSA. In all countries with MRSA
colonization in swine farms, the workers on those farms and their families are found to
test positive in large proportions. Strains of MRSA commonly found on swine farms
and in swine farm workers (specifically ST398), have resistance to many antibiotics, but
one that stands out is tetracycline. Tetracycline is used often in the raising of hogs and
not often used in humans. This has led some researchers to postulate that this strain of
MRSA developed its antibiotic resistance on said farms.
The goal of this paper is to test whether there is a link between the increasing presence
of MRSA on swine farms with the uptick in CA-MRSA using North Carolina hospital
discharge data in logistic regression models and county level data using count and
frac-tional models. The results of this paper show whether a person’s proximity to swine
farms and concentration of said swine farms is related to their likelihood of contracting
CA-MRSA. This has many implications for public health officials. With the increasing
numbers of CA-MRSA infections and the high number of people dying from MRSA
Chapter 2
The Price Impact of an Embargo:
The 1973 Soybean Embargo in the
United States
2.1
Introduction
In mid-1973, soybeans in the United States were in short supply and prices were increasing
quickly. The failure of the Peruvian anchovy catch in 1972 dramatically decreased the
availability of high-protein feed for livestock and thereby greatly increased demand for
soybean meal, a high-protein substitute in feed. In January 1973, the USDA released
restrictions on “set-aside” cropland1 to help ease the tensions in the market and increase
1“Set-aside was an agricultural policy that required farmers to set aside a certain percentage of their
total planted acreage to devote to approved conservation uses. The policy has not been used since the late 1970s and authority for “set-aside” was eliminated by the 1996 Farm Bill.
the production of soybeans. To make matters worse, flooding hindered planting in the
spring of 1973. Furthermore, the U.S. dollar was devalued against major trading partners
by approximately ten percent on February 15, 1973, contributing to a marked increase
in foreign demand for U.S. exports.
As an attempt to stabilize prices and ensure adequate domestic supply, the United
States implemented an export embargo of soybeans, cottonseed and their byproducts on
June 27, 1973. This was carried out under the ”short supply” provision of The Export
Administration Act of 1969, which delegated the authority to control exports from the
United States for three purposes:
“(A) to the extent necessary to protect the domestic economy from the
exces-sive drain of scarce materials and to reduce the serious inflationary impact of
abnormal foreign demand, (B) to the extent necessary to further significantly
the foreign policy of the United States and to fulfill its international
respon-sibilities, and (C) to the extent necessary to exercise the necessary vigilance
over exports from the standpoint of their significance to the national security
of the United States.”2
The response from importers of these goods was so intense, namely Japan and European
countries, the embargo was swiftly lifted less than one week later, on July 2, 1973.
The embargo was replaced with an export-licensing system. Export licenses were
issued against each contract for 50 percent of unfilled soybean contracts and 40 percent of
unfilled meal and cake contracts. This strict licensing system was relaxed for soybean meal
and cake in August and in September for soybeans. Licensing was altogether discontinued
on September 21, 1973. This coincided with the new soybean harvest in the United States.
This embargo was not only short; it actually did not impact any contracted shipments
to the largest importer of United States’ soybeans, Japan. In 1973, Japan, in the midst
of an already highly inflationary period, obtained over 88 percent of its soybean imports
from the United States. This was approximately 84 percent of its total supply of soybeans.
A disruption in supply of soybeans from the United States would have been detrimental
to Japan as soybeans were (and still are) a major staple of the country’s diet. It was also
used extensively in animal feed. It is important to note that there are differences in
feed-grade and food-feed-grade soybeans. Six percent of Japan’s supply of soybeans was produced
domestically at this time. In addition, the United States produced approximately 68
percent of the world’s soybeans during this period.
The embargo came without warning for Japan, and there were fears about future
disruptions to trade between the United States and Japan. To ease tension, even after
the end of the embargo and licensing period, Secretary of Agriculture, Earl Butz, visited
the Japanese Minister of Agriculture, Tadao Kuraishi, in Tokyo in April 1974 to guarantee
the Japanese government of the reliability of American exports. These guarantees were
followed by the Butz-Abe Agreement in 1975; a bilateral agreement that set minimum
annual quantities of wheat, feed grains and soybeans the United States would supply to
Japan over the 1976-1978 period. All of these minimum quantities were exceeded in all
of the years of the agreement.
Since the embargo was so short and did not impact any contracted shipments, I
investigate whether or not it was still able to impact the price of soybeans. As it turns
out, the embargo was able to temporarily stabilize prices, but once it’s short duration
was discovered, uncertainty intensified immensely, and prices increased even more.
Embargoes are relatively rare in United States’ history, but are more common in
other countries, especially developing countries. In this particular case, the United States
enacted a ban on the trade of soybeans and its byproducts as well as cottonseed and
its byproducts with all countries. This was put into effect due to a shortage of soybeans
at home as well as an attempt to stabilize prices. This was essentially a food security
issue. Some embargoes are put in to place for political reasons as opposed to food security
reasons. The issue with embargoes is that they cause increased volatility in a market. They
also cause the enacting country to be viewed as an unreliable supplier. Thinking about
this from the other country’s side (in this case think of Japan), these extreme non-tariff
barriers are a justification for the role of government intervention in agricultural markets.
Japan had very little domestic production of soybeans and essentially one supplier. An
argument could be made for government intervention to encourage increased growth at
home and for the diversification of suppliers.
In the following sections, I explore the price impact of the embargo on soybean prices.
Section 2.2 details the background and methodology, Section 2.3 presents the data and
results, Section 2.4 continues with a discussion of the results and Section 2.5 concludes
2.2
Background and Methodology
I follow a similar econometric model to that of a differnce-in-differences model. I use a
relative price of a substitute good method to estimate the price impact of the embargo,
as in Carter and Smith (2007). I compare the prices of soybeans to those of a primary
substitute, corn. Corn is a valid substitute for soybeans due to the fact that they are
production substitutes, as well as both used primarily for animal feed. Corn is used as a
calorie supplement and soymeal is used as a protein source. Also, corn was not affected
by the embargo in 1973. Essentially, corn is used as the control in this model.
The relative price of a substitute method exploits the time series properties of the
price of a commodity considered relative to the price of a substitute good to infer the
price impact of an event that did not impact the substitute good. This allows general
market fluctuations to be accounted for without the need for a formal structural supply
and demand model to be developed. To see the relative price dynamics of the two goods,
the relative price of the two goods must be stable prior to the event of interest. Once
shown stable, any change in the relative price implies a change in the underlying supply
and demand relationship. This allows for a direct estimation of the price impact of the
event.
I apply time-series analysis techniques appropriate for nonstationary and potentially
cointegrated price series in measuring the impacts of the embargo on equilibrium price
relationships. The ”event study” analysis begins with an analysis of long-run structural
breaks at known and unknown joint points. To this end, I apply a conventional Chow
test for known structural breaks as well as the structural change tests of Hansen (1992),
Hansen (2001), Andrews, Lee and Ploberger (1996), Ploberger and Kramer (1992), Bai
and Perron (1998) and Bai and Perron (2003). The latter tests are appropriate when the
timing of a structural break is a priori unknown. In such a case, such Chow-type tests
have nonstandard distributions due to the presence of parameters that are unidentified
under the null hypothesis of no structural break.
Upon confirming the presence of a statistically significant structural break, I
under-take estimation that identifies the multiple regimes corresponding to the periods before
and after the embargo. The dynamics of adjustments to market shocks across different
commodity markets are evaluated. The embargo and its implications for the substantial
rise in the prominence of Brazilian soybean exports and the concomitant adjustments
realized in the United States’ export market are discussed in Section 2.4.
2.3
Data and Results
My analysis uses daily cash closing price data from the Chicago Board of Trade for
Chicago #2 soybeans and Chicago #2 yellow corn. The price of soybeans tended to
move with corn prices before the embargo. The relative prices were very stable. Figure
1 shows the prices of soybeans and corn in log terms prior to the embargo. In 1962,
the soybean harvest was approximately 19% of the corn harvest and by 1972 it was
approximately 27%. Soybean production increased about 69% during this period while
corn increased only 15%. Even as production changed drastically, relative prices stayed
rather stable showing that demand for soybeans and corn was elastic, implying close
substitutability. From 1962 to 1970 the average log price difference between soybeans and
was 1.1551, or about 115.51%. Thus, soybeans went from having a 79.66% premium over
corn to having a 115.51% premium.
To illustrate the long-run stability in the relative price of soybeans to corn, prior to
the embargo, I show that absolute soybean and corn prices were cointegrated with a (1,
-β) cointegrating vector. A pair of time series data are cointegrated if they have a common
stochastic trend as shown in Engle and Granger (1987). When viewed separately, each
series exhibits a stochastic trend or a unit root, but when viewed as a linear combination
of the series, there is no unit root or trend. Here, the cointegration between soybeans and
corn can be represented by the following model:
st=µ+βct+zt (2.1)
wherestdenotes the log price of soybeans,ctis the log price of corn, andztis a stationary
error term. Now, I apply the augmented Dickey-Fuller test to the log price of soybeans
and corn separately to demonstrate the presence of a unit root in both series, then to the
log relative price of soybeans to corn to show the lack of a unit root, thus showing the
two series are cointegrated. The results of these tests using data prior to the embargo
(from 1960 - 1972) are presented in Table 2.1. The tests show that the prices of soybeans
and corn were cointegrated prior to 1973.
To start with the breaks testing, I run a standard Chow test for one known break at
the time of the embargo. Based on the results, I reject the null hypothesis of no structural
break at the time of the embargo. Next, I use the structural breaks tests of Bai and Perron
(1998 and 2003) to determine whether or not the log relative price stayed stable beyond
1972, through the period containing the embargo. To do this, I expand the sample of
data to include the embargo, through 1975. A break in the relative price of soybeans to
corn would indicate that whatever shock caused the break had a lasting impact on the
long-run pricing relationship. Since the data were cointegrated prior to 1973, this would
suggest that there were no pre-1973 breaks, otherwise the series would not have been
cointegrated. Thus, the breaks tests provide a robustness check on the aforementioned
cointegration results.
First, break dates are determined using an algorithm developed by Bai and Perron
(2003). The algorithm computes estimates of break points that are global minimizers
of the sum of squared residuals based on the principle of dynamic programming. For
each number of breaks, m, parameters are estimated and the resulting residual sum of
squares is stored. For each number of breaks, the estimated regression that minimizes
the residual sum of squares is selected. Then to select the number of breaks, I use the
Bayesian Information Criterion (BIC) from the estimated regression for each number of
breaks. The BIC is minimized at one break as shown in Table 2.2. I also test for breaks
using sequential sup-F tests and recursive estimates tests and these tests confirm the
presence of just one break3. This procedure provides strong evidence of one break in
early July 1973. This is after the announcement (and end) of the embargo.
The finding of a break in mid July is corroborated by Figure 2.2, which shows the log
relative price of soybeans and corn through the entire sample. The relative price stayed
rather stable through the pre-embargo period, then around the break date found by the
Bai and Perron process, which is referenced by the vertical line, the log relative price
increased substantially.
Next, I want to analyze the price impact of this event. To do so, I form a vector error
correction model (VECM) for forecasting. The VECM is:
∆st=αszt−1+γs(L)∆st−1+δc(L)∆ct−1+st (2.2)
∆ct=αczt−1+γc(L)∆ct−1 +δs(L)∆st−1+st
where γs(L), δs(L), γc(L), δc(L) are polynomials in the lag operator andzt =st−ct−µ
is the error correction term. The parameters αsand αcare terms measuring the response
of soybean and corn prices to deviations from the long-run trend. The closer these values
are to zero, the longer it takes for the series to return to the long-run trend after a shock.
The results of the estimation of equation (2.2) are in Table 2.3 using data through 1973
(before the embargo).
The error correction parameter for soybeans,αs, is -0.00016, which is not significantly
different from zero. The error correction parameter for corn,αc, is 0.0039. This indicates
that on average the daily price of corn changes to correct any deviation from long-run
trend by 0.39%. This is very small and suggests a slow reversion, but it is significantly
different from zero. This suggests that soybean and corn can deviate from the long-run
stable relationship for long periods of time, but eventually retire to a stable equilibrium
relationship. Calculating a half-life from the error correction parameter for corn, it takes
178 days, approximately 35 to 36 weeks for prices to return to the long-run stable trend.
Using the estimates from the VECM, I compute forecasts of the log prices of
soy-beans and corn over the window of the embargo and beyond. The abnormal returns are
calculated as the difference between the forecasted values and the observed values as
ARs
t = ∆st−∆ˆst−1 for soybeans and ARct = ∆ct−∆ˆct−1 for corn. The results of this
are shown in Figure 2.3. If one sums over the window of interest, cumulative abnormal
returns are revealed as
CARs =
k
X
t=s
(∆st−∆ˆst−1) =sk−sˆk (2.3)
CARc =
k
X
t=s
(∆ct−∆ˆct−1) = ck−ˆck
where s is the start of the window and k is the end. Therefore, the CAR is the error in
forecast of soybean or corn prices at the end of the window. Note that my definition of
CAR is not the same as traditional event studies, but better fits the analysis performed
in this paper. The CAR for soybeans and corn with confidence intervals are presented
in Figure 2.4 and 2.5, respectively. Both corn and soybean prices are well above their
forecasted values for the whole period of the embargo and export license system, but
until mid-September, the CAR of soybeans was much above the CAR of corn. On the
day that the embargo was enacted, the CAR of the log price of soybeans was 0.8893 while
the CAR of the log price of corn was only 0.4008. By July 5th, days after the embargo
officially ended, the CAR of the log price of soybeans was down to 0.4089, very close to
corn which was 0.3501. It would appear that the embargo was able to calm some of the
drastic rise in domestic prices. After the end of the embargo and the start of the export
licensing system, both corn and soybean prices increased. The CAR for soybeans show
that on average the log price of soybeans was approximately 0.5235 above its predicted
Next, I run the whole process again with soybean prices received by farmers from
the USDA National Agricultural Statistics Service (NASS) and with Rotterdam, c.i.f.
monthly soybean prices from the World Bank. These data span from January 1960
through December 1989 to ensure a substantial number of observations.
The Rotterdam monthly soybean prices with the NASS soybean prices reveal similar
results. The two series are plotted in Figure 2.6 with the embargo month highlighted.
The results of Augmented Dickey-Fuller tests are in Table 2.4. The log of domestic
monthly soybean prices and the log of Rotterdam monthly soybean prices both show
the presence of a unit root, but the log relative price of the two series does not have
a unit root and are therefore the prices are cointegrated, thus implying a cointegrating
vector of [1,−1]. The Bai and Perron test shows one break in April 1973. This is shown
in Figure 2.7. Once again, the vector error correction model estimates are presented
in Table 2.5. The error correction parameter for domestic soybeans, αd, is -0.2895 and
is significant at a ten percent level. This indicates that the average monthly price of
domestic soybeans changes to correct any deviation from the long-run trend by about
-28.95%. The error correction parameter for Rotterdam soybeans, αe, is 0.4185, which
is not statistically different from zero. The half-life calculation from the error correction
parameter on domestic soybeans implies that it takes almost 3 months for prices to return
to the long-run stable relationship. The forecasts for monthly prices during the period of
the embargo from the VECM are in Figure 2.8.
The cumulative abnormal returns for domestic soybeans and Rotterdam soybeans are
in Figures 2.9 and 2.10, respectively. These show something quite interesting. In April
1973, when the break was estimated by the Bai and Perron tests, the CAR for domestic
log soybean prices was 0.3063 and 0.3410 for Rotterdam prices. In May both CAR’s had
almost doubled to 0.5999 for domestic prices and 0.6621 for Rotterdam prices. By June,
when the embargo was put into place, the domestic CAR increased to only 0.7824, while
the Rotterdam CAR increased to 0.9317. Following this marked increase for both sets
of prices, July’s domestic CAR was 0.3743 and 0.5750 for Rotterdam prices. This would
appear to indicate that the embargo stabilizing domestic prices, while not impacting the
Rotterdam price as much.
Rotterdam represents a global price discovery point for soybeans. In the 1973/1974
production year the United States produced approximately 78 percent of the soybeans
in the world according to the USDA Foreign Agricultural Service. As the United States
was the majority producer of soybeans, it is not surprising that changes in the price
of United States’ soybeans affected the Rotterdam price of soybeans. Interestingly, the
United States’ market share for soybeans started to drop in 1975, coinciding with the
advent of the Brazilian soybean market, in which Japan was a major investor.
Finally, as a robustness check, I run the analysis on NASS soybean and corn monthly
prices. The data span from January 1960 through December 1989 as with the Rotterdam
analysis. Figure 11 plots the monthly log prices of soybeans and corn. Table 6 presents
the results of the Augmented Dickey-Fuller tests. Both the log of soybean monthly prices
and the log of monthly corn prices exhibit a unit root, but the log difference of the
two series do not, thus suggesting that they are cointegrated series with a cointegrating
vector of [1,−1]. It is clear from the figure that there is indeed a structural break in the
relationship between the prices. The results of the breaks tests are remarkably similar to
Perron test for unknown breaks reveals one break in the log relative price of soybeans
and corn. This break is in March 1973, just before the embargo. The break is plotted in
the log relative prices in Figure 2.12. This pre-embargo break in monthly prices further
proves a substantial change in the conditions of the soybean market. The fact that it
occurs before the embargo implies that the market was already in the process of a change
before the embargo was implemented. This could be the policy being anticipated by the
market.
The vector error correction model estimates are presented in Table 2.7. The error
correction parameter for soybeans, αs, is -0.139, which is not significantly different from
zero. The error correction parameter for corn,αc, is 0.0934. This indicates that on average
the monthly price of corn changes to correct any deviation from long-run trend by 9.34%.
The forecasts from the VECM for the period of the embargo are in Figure 2.13. The
half-life from the error correction parameter for corn implies that it takes between 7 and 8
months for prices to return to the long-run stable relationship.
2.4
Discussion
In this paper, I have used the relative price of a substitute method developed by Carter
and Smith (2007) to show the impact of a very short embargo on the price of soybeans.
This approach is quite novel, and allows for estimation of a price impact without the
need for a formal structural supply and demand model. This is attractive because any
misspecification in the structural model will bias the results. This method, by using a
substitute good, allows for general market fluctuations to be accounted for while teasing
out the event that happened to the commodity of interest.
I use the relative price of a substitute good method to estimate the price impact of this
embargo with daily price data. Initially, using corn as a substitute not impacted by the
embargo, I am able to capture the relative change in the price of soybeans. I apply
time-series analysis techniques appropriate for nonstationary and cointegrated prices time-series in
measuring the impacts of the embargo on equilibrium price relationships. Testing for
long-run structural breaks at known and unknown points is done, followed by the estimation
of a vector error correction model that allows the creation of forecasts for the prices had
such a break not occurred. The forecast error from this model is used to estimate the
price impact of the embargo. The process is repeated with monthly prices for corn and
soybeans as well as with monthly domestic and export prices for soybeans.
The VECM models in all cases above forecasted soybean prices to be lower than what
happened in reality. The daily data showed a break happening after the embargo had
ended, but still during the export licensing program. The monthly data for soybeans and
corn showed the break happening just before the embargo began, similar to the results
from the Rotterdam and domestic soybean analysis. These results show that there was
indeed a structural change in the market for soybeans around the time of the embargo
being enacted.
The embargo did in fact have an impact on the price of soybeans, a statistically
significant one at that. From the daily price analysis, the cumulative abnormal return
calculated from the vector error correction model of the log price of soybeans was much
above that of corn. On the day that the embargo was enacted, the CAR of soybeans
embargo was lifted, the CAR of soybeans was 0.4089, close to the CAR of corn, 0.3501.
After the embargo the CAR of soybeans increased. From January 1973 through the end
of the export licensing system, the CAR for soybeans and corn show that on average the
log price of soybeans was approximately 0.5235 above its predicted value and the average
log price of corn was approximately 0.2531 above its predicted value. These results are
very similar to the monthly price analysis for both soybean and corn prices as well as the
Rotterdam and domestic soybean prices.
The relationship between the United States and Japan was disturbed by the
im-position of an embargo in June of 1973. Since the embargo came without warning for
Japan, there were fears about further disruptions to trade between the two countries.
Even though efforts were made to minimize the impacts on the Japanese, Japan made
strategic investments to diversify the supply of soybeans in the future by investing heavily
in the infant Brazilian soybean market. Brazil now is second only to the United States
in soybean production.
Using the soybean embargo as a starting point, I looked to other embargoes by the
United States. The wheat embargo to the Soviet Union in 1980 is one example. I ran the
above analysis on this event and found that it did not impact wheat prices (using corn as
a substitute) in the way that soybeans were impacted. Wheat and corn were cointegrated
over the period leading up the the wheat embargo. With this result in hand, the relative
price of a substitute good method revealed that there was in fact no price impact from
the wheat embargo. First, I used a standard Chow test for one known break at the time
of the embargo. I was unable to reject the null hypothesis of no structural break at the
time of the embargo against the Soviet Union. To ensure there were no breaks around this
time, I used the Bai and Perron test for unknown structural breaks. Again, I was unable
to reject the first null hypothesis of no structural break over the whole time period which
was from 1960 through 1999. This makes sense because the embargo only was placed
against one country and there were many options for wheat for the Soviet Union outside
of the United States such as Canada, Argentina, and Australia. There are also indications
that the Soviet Union was able to skirt the embargo by the use of intermediaries. This
embargo, unlike the soybean embargo, was put in to place for political reasons as well.
2.5
Concluding Remarks
The purpose of this paper was to test if the soybean embargo of 1973 had a price impact
on the market price of soybeans even though it did not impact any contracted shipments.
While the results show that the embargo was able to stabilize prices for a very short period
of time, the aftermath was substantially higher prices. The embargo and the export
licensing system appear to have increased uncertainty even more than the other market
conditions and therefore caused prices to increase further. This shows that policy makers
should exercise caution when enacting trade policies of this sort. Even short embargoes
that do not impact any contracted shipments are able to exacerbate uncertainty and
cause our trading partners to seek diversity in sources for necessities like Japan did with
investing in the Brazilian soybean market.
Embargoes are relatively rare in United States’ history, but are more common in
other countries, especially developing countries. In this particular case, the United States
byproducts with all countries. This was put into effect due to a shortage of soybeans at
home as well as an attempt to stabilize prices. This was essentially a food security issue.
Some embargoes are put in to place for political reasons as opposed to food security
reasons. The issue with embargoes is that they cause increased volatility in a market.
They also cause the enacting country to be viewed as an unreliable supplier. The purpose
of this paper was to analyze whether or not this particular embargo was able to do what
it set out to: stabilize prices. It did.
The implications for unexpected trade embargoes are large and in the future I plan to
analyze the rise in the Brazilian soybean market and its impact on the United States’
soy-bean market. Using a structural model, I plan to investigate how non-tariff barriers such
as embargoes impact the market share of countries’ exports for different commodities,
and if barriers to one commodity affect other commodities.
Table 2.1: Cointegration Tests on Daily Prices
Test Statistic 5% Critical Value Conclusion
Log Soybeans -1.34 -2.86 Unit Root
Log Corn -2.71 -2.86 Unit Root
Log Difference -2.92 -2.86 Cointegrated
Note: All ADF tests include an intercept, no trend, and 5 lags (as determined by FPE,
Table 2.2: Determination of Number of Structural Breaks
Number of Breaks BIC
0 -21,749.29
1 -21,849.36
2 -21,833.15
3 -21,782.34
4 -21,734.07
5 -21,682.87
Note: Modeled using the log difference of soybeans and corn with 5 lags (as determined
by FPE, AIC and LR).
Table 2.3: Pre-Embargo Vector Error Correction Model Estimates For Daily Prices
Parameter Soybeans Corn
α -0.0016 0.0039**
γ1 -0.0337* 0.0153
γ2 -0.0465** 0.0105
γ3 0.0486* 0.0180
γ4 0.0059 0.0552**
δ1 0.0292 0.0438**
δ2 0.0300* -0.0170
δ3 0.0094 -0.0078
δ4 0.0094 -0.0146
Note: Sample period is 1960-1972. Estimation by Johansen’s (1995) maximum likelihood
Table 2.4: Cointegration Tests for Monthly Domestic and Rotterdam Soybean Prices
Test Statistic 5% Critical Value Conclusion
Log Domestic Soybeans -1.809 -2.887 Unit Root
Log Rotterdam Soybeans -1.104 -2.887 Unit Root
Log Difference -3.934 -2.887 Cointegrated
Note: All ADF tests include an intercept, no trend, and 3 lags (as determined by FPE,
AIC and LR). Log Difference is log(Soybeans/Corn).
Table 2.5: Pre-Embargo Vector Error Correction Model Estimates for Monthly Domestic and Rotterdam Soybean Prices
Parameter Domestic Soybeans Rotterdam Soybeans
α -0.2895* 0.4185
γ1 0.0449 0.5580**
γ2 -0.3202** -0.0316
δ1 0.5361** -0.0511
δ1 0.1548 -0.1231
Note: Sample period is 1960-1972. Estimation by Johansen’s (1995) maximum likelihood
Table 2.6: Cointegration Tests for Monthly Soybean and Corn Prices
Test Statistic 5% Critical Value Conclusion
Log Soybeans -1.409 -2.887 Unit Root
Log Corn -2.448 -2.887 Unit Root
Log Difference -3.421 -2.887 Cointegrated
Note: All ADF tests include an intercept, no trend, and 4 lags (as determined by FPE,
AIC and LR). Log Difference is log(Soybeans/Corn).
Table 2.7: Pre-Embargo Vector Error Correction Model Estimates for Monthly Soybean and Corn Prices
Parameter Soybeans Corn
α -0.139 0.0934**
γ1 0.543** 0.278**
γ2 -0.3114** -0.1271
γ3 0.1395 0.1760**
δ1 -0.0136 0.1473*
δ2 -0.0155 -0.0216
δ3 -0.0513 -0.1029
Note: Sample period is 1960-1972. Estimation by Johansen’s (1995) maximum likelihood
4.5 4. 5 4.5 5 5 5 5.5 5. 5 5.5 6 6 6 01jul1962 01jul1962 01jul1962 01jan1963 01jan 1963 01jan1963 01jul1963 01jul1963 01jul1963 01jan1964 01jan 1964 01jan1964 01jul1964 01jul1964 01jul1964 01jan1965 01jan 1965 01jan1965 01jul1965 01jul1965 01jul1965 01jan1966 01jan 1966 01jan1966 01jul1966 01jul1966 01jul1966 01jan1967 01jan 1967 01jan1967 01jul1967 01jul1967 01jul1967 01jan1968 01jan 1968 01jan1968 01jul1968 01jul1968 01jul1968 01jan1969 01jan 1969 01jan1969 01jul1969 01jul1969 01jul1969 01jan1970 01jan 1970 01jan1970 01jul1970 01jul1970 01jul1970 01jan1971 01jan 1971 01jan1971 01jul1971 01jul1971 01jul1971 01jan1972 01jan 1972 01jan1972 01jul1972 01jul1972 01jul1972 time time time Log Soybean Log Soybean Log Soybean Log Corn Log Corn Log Corn
Log Soybean and Log Corn Prices Pre-Embargo 1962-1972
Log Soybean and Log Corn Prices Pre-Embargo 1962-1972
Log Soybean and Log Corn Prices Pre-Embargo 1962-1972
Figure 2.1: Daily Log Prices Before Event
July 12, 1973
July 12, 1973 July 12, 1973
.6 .6 .6 .8 .8 .8 1 1 1 1.2 1. 2 1.2 1.4 1. 4 1.4 1.6 1. 6 1.6 Log Difference Log D iff er en ce Log Difference 01jan1960 01jan 1960 01jan1960 01jan1961 01jan 1961 01jan1961 01jan1962 01jan 1962 01jan1962 01jan1963 01jan 1963 01jan1963 01jan1964 01jan 1964 01jan1964 01jan1965 01jan 1965 01jan1965 01jan1966 01jan 1966 01jan1966 01jan1967 01jan 1967 01jan1967 01jan1968 01jan 1968 01jan1968 01jan1969 01jan 1969 01jan1969 01jan1970 01jan 1970 01jan1970 01jan1971 01jan 1971 01jan1971 01jan1972 01jan 1972 01jan1972 01jan1973 01jan 1973 01jan1973 01jan1974 01jan 1974 01jan1974 01jan1975 01jan 1975 01jan1975 time time time
Log Relative Prices (Soybean/Corn) by Day
Log Relative Prices (Soybean/Corn) by Day
Log Relative Prices (Soybean/Corn) by Day
6 6 6 6.5 6. 5 6.5 7 7 7 5 5 5 5.5 5. 5 5.5 6 6 6 12/13/72 12/ 13/ 72 12/13/72 2/28/73 2/28/ 73 2/28/73 5/10/73 5/10/ 73 5/10/73 7/24/73 7/24/ 73 7/24/73 10/3/73 10/ 3/73 10/3/73 12/13/72 12/ 13/ 72 12/13/72 2/28/73 2/28/ 73 2/28/73 5/10/73 5/10/ 73 5/10/73 7/24/73 7/24/ 73 7/24/73 10/3/73 10/ 3/73 10/3/73
Forecast for Log Soybean Prices
Forecast for Log Soybean Prices Forecast for Log Soybean Prices
Forecast for Log Corn Prices
Forecast for Log Corn Prices Forecast for Log Corn Prices
95% CI 95% CI 95% CI forecast forecast forecast observed observed observed
Figure 2.3: Forecasted Daily Prices from VECM with Observed Prices
-.5
-.5
-.5 0
0
0 .5
.5
.5 1
1
1
01jan1973
01jan1973 01jan1973 01apr1973
01apr1973 01apr1973
01jul1973
01jul1973 01jul1973
01oct1973
01oct1973 01oct1973
time
time time
CAR Log Soybean
CAR Log Soybean CAR Log Soybean
95% Confidence Interval
95% Confidence Interval 95% Confidence Interval
Cumulative Abnormal Returns for Log Soybean Prices
Cumulative Abnormal Returns for Log Soybean Prices
Cumulative Abnormal Returns for Log Soybean Prices
-.2 -.2 -.2 0 0 0 .2 .2 .2 .4 .4 .4 .6 .6 .6 .8 .8 .8 01jan1973 01jan1973 01jan1973 01apr1973 01apr1973 01apr1973 01jul1973 01jul1973 01jul1973 01oct1973 01oct1973 01oct1973 time time time
CAR Log Corn
CAR Log Corn CAR Log Corn
95% Confidence Interval
95% Confidence Interval 95% Confidence Interval
Cumulative Abnormal Returns for Log Corn Prices
Cumulative Abnormal Returns for Log Corn Prices
Cumulative Abnormal Returns for Log Corn Prices
Figure 2.5: Cumulative Abnormal Returns for Log(Corn)
June 1973 June 1973 June 1973 .5 .5 .5 1 1 1 1.5 1. 5 1.5 2 2 2 2.5 2. 5 2.5 01jan1960 01jan 1960 01jan1960 01jan1962 01jan 1962 01jan1962 01jan1964 01jan 1964 01jan1964 01jan1966 01jan 1966 01jan1966 01jan1968 01jan 1968 01jan1968 01jan1970 01jan 1970 01jan1970 01jan1972 01jan 1972 01jan1972 01jan1974 01jan 1974 01jan1974 01jan1976 01jan 1976 01jan1976 01jan1978 01jan 1978 01jan1978 01jan1980 01jan 1980 01jan1980 01jan1982 01jan 1982 01jan1982 01jan1984 01jan 1984 01jan1984 01jan1986 01jan 1986 01jan1986 01jan1988 01jan 1988 01jan1988 01jan1990 01jan 1990 01jan1990 time time time Rotterdam Rotterdam Rotterdam Domestic Domestic Domestic
Log Rotterdam Soy and Log Domestic Soy Prices by Month
Log Rotterdam Soy and Log Domestic Soy Prices by Month
Log Rotterdam Soy and Log Domestic Soy Prices by Month
April 1973 April 1973 April 1973 -.4 -.4 -.4 -.3 -.3 -.3 -.2 -.2 -.2 -.1 -.1 -.1 0 0 0
Log Difference D-R
Log D iff er en ce D -R
Log Difference D-R 01jan1960 01jan 1960 01jan1960 01jan1962 01jan 1962 01jan1962 01jan1964 01jan 1964 01jan1964 01jan1966 01jan 1966 01jan1966 01jan1968 01jan 1968 01jan1968 01jan1970 01jan 1970 01jan1970 01jan1972 01jan 1972 01jan1972 01jan1974 01jan 1974 01jan1974 01jan1976 01jan 1976 01jan1976 01jan1978 01jan 1978 01jan1978 01jan1980 01jan 1980 01jan1980 01jan1982 01jan 1982 01jan1982 01jan1984 01jan 1984 01jan1984 01jan1986 01jan 1986 01jan1986 01jan1988 01jan 1988 01jan1988 01jan1990 01jan 1990 01jan1990 time time time
Log Relative Prices (domestic/export) by Month
Log Relative Prices (domestic/export) by Month
Log Relative Prices (domestic/export) by Month
Figure 2.7: Monthly Log Relative Prices of Domestic Soy and Export Soy
1 1 1 1.5 1. 5 1.5 2 2 2 2.5 2. 5 2.5 1 1 1 1.5 1. 5 1.5 2 2 2 2.5 2. 5 2.5 May 1972 May 1 972 May 1972 April 1973 April 1 973 April 1973 Jan 1974 Jan 1 974 Jan 1974 Nov 1974 Nov 197 4 Nov 1974 May 1972 May 1 972 May 1972 April 1973 April 1 973 April 1973 Jan 1974 Jan 1 974 Jan 1974 Nov 1974 Nov 197 4 Nov 1974
Forecast for Domestic Prices
Forecast for Domestic Prices Forecast for Domestic Prices
Forecast for Rotterdam Prices
Forecast for Rotterdam Prices Forecast for Rotterdam Prices
95% CI 95% CI 95% CI forecast forecast forecast observed observed observed
-.5 -.5 -.5 0 0 0 .5 .5 .5 1 1 1 April 1973 April 1 973 April 1973 May 1973 May 1 973 May 1973 June 1973 June 197 3 June 1973 July 1973 July 1 973 July 1973 Aug 1973 Aug 1 973 Aug 1973 Sept 1973 Sept 197 3 Sept 1973 time time time
CAR Domestic Soybeans
CAR Domestic Soybeans CAR Domestic Soybeans
95% Confidence Interval
95% Confidence Interval 95% Confidence Interval
Cumulative Abnormal Returns for Log(Soybean) Prices
Cumulative Abnormal Returns for Log(Soybean) Prices
Cumulative Abnormal Returns for Log(Soybean) Prices
Figure 2.9: Cumulative Abnormal Returns for Monthly Domestic Log Soybean Prices
-.5 -.5 -.5 0 0 0 .5 .5 .5 1 1 1 April 1973 April 1 973 April 1973 May 1973 May 1 973 May 1973 June 1973 June 197 3 June 1973 July 1973 July 1 973 July 1973 Aug 1973 Aug 1 973 Aug 1973 Sept 1973 Sept 197 3 Sept 1973 time time time
CAR Rotterdam Soybeans
CAR Rotterdam Soybeans CAR Rotterdam Soybeans
95% Confidence Interval
95% Confidence Interval 95% Confidence Interval
Cumulative Abnormal Returns for Log(Rotterdam) Prices
Cumulative Abnormal Returns for Log(Rotterdam) Prices
Cumulative Abnormal Returns for Log(Rotterdam) Prices
0 0 0 .5 .5 .5 1 1 1 1.5 1. 5 1.5 2 2 2 2.5 2. 5 2.5 01jan1960 01jan 1960 01jan1960 01jan1962 01jan 1962 01jan1962 01jan1964 01jan 1964 01jan1964 01jan1966 01jan 1966 01jan1966 01jan1968 01jan 1968 01jan1968 01jan1970 01jan 1970 01jan1970 01jan1972 01jan 1972 01jan1972 01jan1974 01jan 1974 01jan1974 01jan1976 01jan 1976 01jan1976 01jan1978 01jan 1978 01jan1978 01jan1980 01jan 1980 01jan1980 01jan1982 01jan 1982 01jan1982 01jan1984 01jan 1984 01jan1984 01jan1986 01jan 1986 01jan1986 01jan1988 01jan 1988 01jan1988 01jan1990 01jan 1990 01jan1990 time time time Log Corn Log Corn Log Corn Log Soybean Log Soybean Log Soybean
Log Corn and Log Soybean Prices by Month
Log Corn and Log Soybean Prices by Month
Log Corn and Log Soybean Prices by Month
Figure 2.11: Monthly Log Prices of Soy and Corn
March 1973 March 1973 March 1973 .6 .6 .6 .8 .8 .8 1 1 1 1.2 1. 2 1.2 1.4 1. 4 1.4 1.6 1. 6 1.6 Log Difference Log D iff er en ce Log Difference 01jan1960 01jan 1960 01jan1960 01jan1962 01jan 1962 01jan1962 01jan1964 01jan 1964 01jan1964 01jan1966 01jan 1966 01jan1966 01jan1968 01jan 1968 01jan1968 01jan1970 01jan 1970 01jan1970 01jan1972 01jan 1972 01jan1972 01jan1974 01jan 1974 01jan1974 01jan1976 01jan 1976 01jan1976 01jan1978 01jan 1978 01jan1978 01jan1980 01jan 1980 01jan1980 01jan1982 01jan 1982 01jan1982 01jan1984 01jan 1984 01jan1984 01jan1986 01jan 1986 01jan1986 01jan1988 01jan 1988 01jan1988 01jan1990 01jan 1990 01jan1990 time time time
Log Relative Prices (soybean/corn) by Month
Log Relative Prices (soybean/corn) by Month
Log Relative Prices (soybean/corn) by Month
1 1 1 1.5 1. 5 1.5 2 2 2 2.5 2. 5 2.5 0 0 0 .5 .5 .5 1 1 1 1.5 1. 5 1.5 May 1972 May 1 972 May 1972 April 1973 April 1 973 April 1973 Jan 1974 Jan 1 974 Jan 1974 Nov 1974 Nov 197 4 Nov 1974 May 1972 May 1 972 May 1972 April 1973 April 1 973 April 1973 Jan 1974 Jan 1 974 Jan 1974 Nov 1974 Nov 197 4 Nov 1974
Forecast for Log Soybean Prices
Forecast for Log Soybean Prices Forecast for Log Soybean Prices
Forecast for Log Corn Prices
Forecast for Log Corn Prices Forecast for Log Corn Prices
95% CI 95% CI 95% CI forecast forecast forecast observed observed observed
Figure 2.13: Forecasted Monthly Prices from VECM with Observed Prices (Soybeans and Corn)
Chapter 3
Modeling Nonlinear Dynamic
Linkages Among Real Interest Rates
3.1
Background
The real interest rate parity (RIP) hypothesis is one of the tenets of international
eco-nomics. Under RIP, well-functioning capital markets would allow for national real interest
rates to be tied to a world interest rate that is determined in the world credit market.
Due to the development of financial markets over the last few decades through the
re-moval of capital controls and other investment barriers, it is likely that capital markets
are more integrated now than in the past. This is important for policy makers, especially
in countries that are small relative to the world credit market, because it ties a country’s
policy instrument to a world interest rate, thus limiting their abilities to effectively enact
policy independently.
A large body of literature has been devoted to the investigation of these international
interest rate linkages. Early studies used conventional regression techniques to test for