- •Preface
- •Contents
- •Chapter 1
- •1.1 International Financial Markets
- •Foreign Exchange
- •Covered Interest Parity
- •Uncovered Interest Parity
- •Futures Contracts
- •1.2 National Accounting Relations
- •National Income Accounting
- •The Balance of Payments
- •1.3 The Central Bank’s Balance Sheet
- •Chapter 2
- •2.1 Unrestricted Vector Autoregressions
- •Lag-Length Determination
- •Granger Causality, Econometric Exogeniety and Causal
- •Priority
- •The Vector Moving-Average Representation
- •Impulse Response Analysis
- •Forecast-Error Variance Decomposition
- •Potential Pitfalls of Unrestricted VARs
- •2.2 Generalized Method of Moments
- •2.3 Simulated Method of Moments
- •2.4 Unit Roots
- •The Levin—Lin Test
- •The Im, Pesaran and Shin Test
- •The Maddala and Wu Test
- •Potential Pitfalls of Panel Unit-Root Tests
- •2.6 Cointegration
- •The Vector Error-Correction Representation
- •2.7 Filtering
- •The Spectral Representation of a Time Series
- •Linear Filters
- •The Hodrick—Prescott Filter
- •Chapter 3
- •The Monetary Model
- •Cassel’s Approach
- •The Commodity-Arbitrage Approach
- •3.5 Testing Monetary Model Predictions
- •MacDonald and Taylor’s Test
- •Problems
- •Chapter 4
- •The Lucas Model
- •4.1 The Barter Economy
- •4.2 The One-Money Monetary Economy
- •4.4 Introduction to the Calibration Method
- •4.5 Calibrating the Lucas Model
- •Appendix—Markov Chains
- •Problems
- •Chapter 5
- •Measurement
- •5.2 Calibrating a Two-Country Model
- •Measurement
- •The Two-Country Model
- •Simulating the Two-Country Model
- •Chapter 6
- •6.1 Deviations From UIP
- •Hansen and Hodrick’s Tests of UIP
- •Fama Decomposition Regressions
- •Estimating pt
- •6.2 Rational Risk Premia
- •6.3 Testing Euler Equations
- •Volatility Bounds
- •6.4 Apparent Violations of Rationality
- •6.5 The ‘Peso Problem’
- •Lewis’s ‘Peso-Problem’ with Bayesian Learning
- •6.6 Noise-Traders
- •Problems
- •Chapter 7
- •The Real Exchange Rate
- •7.1 Some Preliminary Issues
- •7.2 Deviations from the Law-Of-One Price
- •The Balassa—Samuelson Model
- •Size Distortion in Unit-Root Tests
- •Problems
- •Chapter 8
- •The Mundell-Fleming Model
- •Steady-State Equilibrium
- •Exchange rate dynamics
- •8.3 A Stochastic Mundell—Fleming Model
- •8.4 VAR analysis of Mundell—Fleming
- •The Eichenbaum and Evans VAR
- •Clarida-Gali Structural VAR
- •Appendix: Solving the Dornbusch Model
- •Problems
- •Chapter 9
- •9.1 The Redux Model
- •9.2 Pricing to Market
- •Full Pricing-To-Market
- •Problems
- •Chapter 10
- •Target-Zone Models
- •10.1 Fundamentals of Stochastic Calculus
- •Ito’s Lemma
- •10.3 InÞnitesimal Marginal Intervention
- •Estimating and Testing the Krugman Model
- •10.4 Discrete Intervention
- •10.5 Eventual Collapse
- •Chapter 11
- •Balance of Payments Crises
- •Flood—Garber Deterministic Crises
- •11.2 A Second Generation Model
- •Obstfeld’s Multiple Devaluation Threshold Model
- •Bibliography
- •Author Index
- •Subject Index
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2.7. FILTERING |
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and a23 = − b22 + bβ12 . Together you have the VAR(2)
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(2.98) is easier to estimate than the VECM and the standard forecasting formulae for VARs can be employed without modiÞcation.
2.7Filtering
Many international macroeconomic time-series contain a trend. The trend may be deterministic or stochastic (i.e., a unit root process). Real business cycle (RBC) theories are designed to study the cyclical features of the data, not the trends. So in RBC research, the data that is being studied is usually passed through a linear Þlter to remove the low-frequency or trend component of the data. To understand what Þltering does to the data you need to have some understanding of the frequency or spectral representation of time series where we think of the observations as being built up from individual subprocesses that exhibit cycles over di erent frequencies.
Linear Þlters take a possibly two-sided moving average of an original set of observations qt to create a new series q˜t
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which frequency components from the original data that are allowed to pass through and how these frequency components are weighted—that is, are the particular frequency components that are allowed through relatively more or less important than they were in the original data.
68 CHAPTER 2. SOME USEFUL TIME-SERIES METHODS
The Spectral Representation of a Time Series
In section 2.4, a unit-root time series was decomposed into the sum of a random walk and a stationary AR(1) component. Here, we want to think of the time-series observations as being built up of underlying cyclical (cosine) functions each with di erent amplitudes and exhibiting cycles of di erent frequencies. A key question in spectral analysis is, which of these frequency components are relatively important in determining the behavior of the observed time-series?
To Þx ideas, begin with the deterministic time-series, qt = a cos(ωt), where time is measured in years. This function exhibits a cycle every t = 2ωπ years. By choosing values of ω between 0 and π, you can get the process to exhibit cycles at any length that you desire. This is illustrated in Figure 2.1 where q1t = a cos(t) exhibits a cycle every 2π = 6.28 years and q2t = a cos(πt) displays a cycle every 2 years.
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Figure 2.1: |
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Something is clearly missing at this point and it is randomness. We introduce uncertainty with a random phase shift. If you compare q1t = a cos(t) to q3t = a cos(t + π/2), q3t is just q1t with a phase shift (horizontal movement) of π2 . This phase shift is illustrated in Figure 2.2
2.7. FILTERING |
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Figure 2.2: π/2Phase shift. Solid: cos(t), Dashed: cos(t + π/2). |
tion. Let the realization be λ, and form the time-series
qt = a cos(ωt + λ). |
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Once λ is realized, qt is a deterministic function with periodicity 2ωπ and phase shift λ but qt is a random function ex ante. We will need the following two basic trigonometric relations.
Two useful trigonometric relations. Let b and c be constants, and i be the imaginary number where i2 = −1. Then
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cos(b) cos(c) − sin(b) sin(c) |
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(2.102) is known as de Moivre’s theorem. You can rearrange it to get
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29You only need to worry about the interval [0, π] because the cosine function is symmetric about zero—cos(x) = cos(−x) for 0 ≤ x ≤ π
70 CHAPTER 2. SOME USEFUL TIME-SERIES METHODS
Now let b = ωt and c = λ and use (2.101) to represent (2.100) as
qt = a cos(ωt + λ)
= cos(ωt)[a cos(λ)] − sin(ωt)[a sin(λ)].
Next, build the time-series qt = q1t + q2t from the two sub-series q1t and q2t, where for j = 1, 2
qjt = cos(ωjt)[aj cos(λj)] − sin(ωjt)[aj sin(λj)],
and ω1 < ω2. The result is a periodic function which is displayed on the left side of Figure 2.3.
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Figure 2.3: For 0 ≤ ω1 < · · · < ωN ≤ π, qt = |
jN=1 qjt, where qjt = |
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cos(ωjt)[aj cos(λj)] − sin(ωjt)[aj sin(λj)]. Left |
panel: N = 2. Right |
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panel: N = 1000
The composite process with N = 2 is clearly deterministic but if you build up the analogous series with N = 100 of these components, as shown in the right panel of Figure 2.3, the series begins to look like a random process. It turns out that any stationary random process can be arbitrarily well approximated in this fashion letting N → ∞.
2.7. FILTERING |
71 |
To summarize at this point, for su ciently large number N of these underlying periodic components, we can represent a time-series qt as
N |
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qt = cos(ωjt)uj − sin(ωjt)vj, |
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where uj = aj cos(λj) and vj = aj sin(λj), E(u2i ) = σi2, E(uiuj) = 0, i 6= j, E(vi2) = σi2, E(vivj) = 0, i 6= j.
Now suppose that E(uivj) = 0 for all i, j and let N → ∞.30 You are carving the interval into successively more subintervals and are cramming more ωj into the interval [0, π]. Since each uj and vj is associated with an ωj, in the limit, write u(ω) and v(ω) as functions of ω. For future reference, notice that because cos(−a) = cos(a), we
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2dz(ω) − du(ω) i
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Z π eiωt − e−iωt
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0 2
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(50) |
30This is in fact not true because E(uivi) =6 0, but as we let N → ∞, the importance of these terms become negligible.
72 CHAPTER 2. SOME USEFUL TIME-SERIES METHODS
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lim |
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π |
iωtdz(ω). |
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(2.108) |
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qt = N→∞ j=1 aj cos(ωjt + λj) = Z |
π e |
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The point of all this is that any time-series can be thought of as be- |
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ing built up from a set of underlying subprocesses whose individual |
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frequency components exhibit cycles of varying frequency. The other |
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side of this argument is that you can, in principle, take any time-series |
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qt and Þgure out what fraction of its variance is generated from those |
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subprocesses that cycle within a given frequency range. The business |
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cycle frequency, which lies between 6 and 32 quarters is of key interest |
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to, of all people, business cycle researchers. |
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Notice that the process dz(ω) is built up from independent incre- |
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ments. For coincident increments, you can deÞne the function s(ω)dω |
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to be |
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s(ω)dω |
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λ = ω |
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E[dz(ω)dz(λ)] = ( |
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, |
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(2.109) |
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0 |
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otherwise |
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where |
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overbar |
denotes |
the |
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complex conjugate.31 |
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eiωt |
eiωt |
= cos2(ωt) + sin2(ωt) = |
1 at frequency ω, it follows that |
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E[eiωt |
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eiωt |
dz(ω)dz(ω)] = s(ω)dω. |
That is, s(ω)dω is the variance of |
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the ω−frequency component of qt, and is called the spectral density |
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function of qt. Since by (2.108), qt is built up from frequency compo- |
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nents ranging from [−π, π], the total variance of qt must be the integral |
31If a and b are real numbers and z = a + bi is a complex number, the complex conjugate of z is z¯ = a − bi. The product zz¯ = a2 + b2 is real.
2.7. FILTERING |
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73 |
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of s(ω). That is32 |
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π |
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π |
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E(qt2) = E[Z−π eiωtdz(ω) Z−π |
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eiλtdz(λ)] |
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= E[Z |
π |
Z π eiωt |
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dz(ω) |
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eiλt |
dz(λ)] |
Zπ −π −π
=E[dz(ω)dz(λ)]
Z−ππ
= |
s(ω)dω. |
(2.110) |
−π
The spectral density and autocovariance generating functions. The autocovariance generating function for a time series qt is deÞned to be
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∞ |
g(z) = |
γjzj, |
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= |
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j X−∞ |
where γj = E(qtqt−j) is the j-th autocovariance of qt. If we let z = e−iω,
then |
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2π Z |
π g(e−iω)eiωkdω = |
2π j= |
γj Z |
π eiω(k−j)dω. |
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1 |
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∞ |
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− |
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X−∞ |
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Let a = k |
− |
j. Then eiωa = cos(ωa)+i sin(ωa) and the integral becomes, |
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R |
π |
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R |
π |
− |
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π |
π |
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−π cos(ωa)dω +i |
−π sin(ωa)dω = (1/a) sin(aω)|−π −(i/a) cos(aω)|−π. |
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The second term is 0 because cos( |
aπ) = cos(aπ). |
The Þrst term |
is 0 too because the sine of any nonzero integer multiple of π is 0 and a is an integer. Therefore, the only value of a that matters is
a = k |
− |
j = 0, which implies that γ |
= |
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1 |
π g(e−iω)eiωkdω. Setting |
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1 |
kπ |
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2π |
−π |
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t) = |
−π s(ω)dω, so the |
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R |
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k = 0, you have γ0 = Var(qt) = 2π |
π g(e−Riω)dω, but you know that |
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Var(q |
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π |
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− |
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spectral density function is proportional |
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to the |
autocovariance generating function with z = e iω. Notice also, |
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R |
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∞ |
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− |
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that when you set ω = 0, then s(0) = |
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γj. The spectral density |
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j=−∞ |
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function of qt at frequency 0 is the |
same thing as the long-run variance |
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P |
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of qt. It follows that |
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2π Z−π g(e−iω)dω, |
(2.111) |
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Var(qt) = Z−π s(ω)dω = |
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π |
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1 |
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π |
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where g(z) = P∞ γjzj.
j=−∞
32We obtain the last equality because dz(ω) is a process with independent increments so unless λ = ω, Edz(ω)dz(λ) = 0.
(52)
(53)